competition and multilevel technology adoption: a dynamic ...dynamic analysis of electronic medical...
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Competition and Multilevel Technology Adoption: A
Dynamic Analysis of Electronic Medical Records
Adoption in U.S. Hospitals ∗
Yanfei Wang
Business School
Renmin University of China, Beijing, China
August 13, 2019
Abstract
This paper develops and estimates a dynamic oligopoly model, to study the multilevel adop-
tion of Electronic Medical Records (EMR) technologies in U.S. hospitals. I find evidence that
hospitals compete and engage in vertical product differentiation in the adoption process. My
counterfactual experiments show that hospitals’ adoption of a higher level of EMR technolo-
gies is greatly deterred by competitive effects. I conduct various counterfactual experiments to
evaluate the effectiveness and design of the U.S. government’s subsidy policy for EMR adoption
enacted in 2009. A policy strategy capturing market and hospital heterogeneities would have
been more effective. Adoption would be further accelerated if the policy had been passed ear-
lier. In addition, by overlooking competitive effects during the adoption, the effectiveness of the
policy would be over-predicted.
∗This article is a revised version of a chapter from my dissertation at Boston University. I am deeply indebted toMarc Rysman for his continued guidance and support. I thank Randall Ellis and Albert Ma for their commentsand suggestions. I have benefited from conversations with Mo Xiao, Ginger Jin, Christopher Knittel, FrancescoDecarolis, Leila Agha, Philip Haile, Ying Fan, Haizhen Lin, Joris Pinkse, Gautam Gowrisankaran, Chun-Yu Ho, andWei Lin. I also thank the seminar participants at Boston University and Boston College. I also acknowledge theHealth Information Management Systems Society (HIMSS) for providing access to their data. All errors are my own.Address for correspondence: [email protected].
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1 Introduction
By October 2018, more than $30 billion had been spent by the U.S. government to subsidize the
adoption of electronic medical record (EMR) technologies and promote their nationwide imple-
mentation.1 Studies regarding how hospitals make adoption decisions and how they have been
affected by the subsidy policy are crucial for evaluating the policy. However, competitive effects
that may exist during the adoption process have been overlooked by policy-makers. If hospitals
adopt EMR strategically as a result of competition, their behavior could be significantly different
from the scenario in which they make independent decisions. My paper examines and quantifies
the importance of the competitive effects in EMR adoption by developing a dynamic oligopoly
model that takes into account strategic interactions of forward-looking hospitals. Furthermore, the
dynamic structural model that describes hospitals’ adoption behavior allows me to evaluate the
effectiveness and design of the subsidy policy through counterfactual experiments.
EMR technologies refer to a number of applications with various functionalities. Basic appli-
cations such as clinical data repository (CDR) create a real-time database to collect and store
patients’ information. Advanced EMR technologies such as computerized practitioner order en-
try (CPOE) are built upon the basic EMR technologies and help physicians to interact with EMR
data and further improve their healthcare quality. For example, the implementation of CPOE could
alert a physician to potential errors in medication orders and patients’ adverse drug reactions. The
basic applications are the foundation of EMR technologies and must first be installed to ensure the
successful and smooth implementation of advanced EMR technologies. To capture the multilevel
feature of EMR technologies, I categorize the basic EMR technologies, including enterprise EMR,
order entry (OE), CDR, and clinical decision support (CDS), as Level 1 (L1) applications, and the
advanced EMR technologies, including CPOE and physician documentation (PD) as Level 2 (L2)
applications.2, 3
Previous studies show that markets do reward hospitals for their quality investments (e.g.,
Chandra et al., 2016). Through investing on EMR technologies, hospitals could gain a competitive
1https://www.cms.gov/Regulations-and-guidance/legislation/EHRIncentivePrograms/DataAndReports.html,accessed June 20, 2019
2The way to define the basic/advanced applications is consistent with previous literature (see Miller and Tucker,2009; Lee et al., 2013; Dranove et al., 2014; McCullough et al., 2016).
3The functionalities of each application are further explained in Section 2.
1
advantage by achieving higher healthcare quality and attracting more patients. EMR adoption helps
hospitals to improve both health outcomes and patients’ satisfaction during the treatment process,
and a higher-level of EMR adoption is associated with a higher-level of quality. Hospitals with
basic EMR technologies can better consolidate information through digitalization of data, which
helps healthcare providers store, retrieve and examine these data more efficiently. The advanced
EMR technologies help hospitals to further improve healthcare quality by providing physicians
with effective decision support and easy care coordination. For example, some studies find that
CPOE significantly reduces mortality for high-risk patients (McCullough et al., 2016), and reduces
the likelihood of adverse patient safety events, particularly for less complex patients (Freedman
et al., 2018b). In addition, EMR adoption may help patients’ interactions with physicians and
improve patients’ satisfaction during the treatment process. Physicians could have greater and
faster information availability with the help of EMR, and this allows them more time to talk to
patients and address their concerns.4
Although EMR technologies potentially increase hospitals’ demand, the marginal benefits of
adoption may decline over the number of adopters in the market, due to more intense competition.5
Moreover, this multilevel feature of EMR adoption provides hospitals with a source for vertical
product differentiation, as competition would be stronger for hospitals of the same adoption level.6
In other words, hospitals may be less likely to adopt a certain level of EMR technologies if there
are more adopters of this level in the market.
As a result, the first objective of my paper is to examine whether hospitals compete and dif-
ferentiate in the adoption process. Furthermore, I aim to quantify the importance of competitive
effects, particularly for the adoption of L2 EMR, as the national implementation of the advanced
applications, such as CPOE, is one of the primary goals of the government.7 The adoption decisions
4Hsu et al. (2005), studying outpatient visits in a medical office building, find that overall patient satisfaction withvisits increases 7 months after the introduction of health IT, and satisfaction also increases in communication aboutmedical issues and comprehension of decisions made during the visit. DesRoches et al. (2008) find that physicianswho use EMR report positive effects on quality of care and high levels of satisfaction.
5Schmidt-Dengler (2006) studies the adoption of nuclear magnetic resonance imaging by U.S. hospitals in astrategic environment and finds evidence of competitive effects. Tay (2003) also points out that predicted increasesin demand from adopting a health technology fall when neighboring hospitals have the technology.
6An important early model of vertical differentiation is developed by Shaked and Sutton (1982). Empiricalstudies about product differentiation include (Mazzeo, 2002; Seim, 2006; Augereau et al., 2006; Rysman et al.,2019). Particularly in the health industry, Tay (2003) shows that quality differentiation is particularly important inthe hospital market, where the choices of Medicare patients are unaffected by prices; Jin (2005) finds that healthmaintenance organizations use voluntary disclosure of product quality to differentiate from competitors.
7For example, to apply for the Medicare/Medicaid incentive programs, hospitals must use CPOE for medication
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for forward-looking hospitals in a competitive environment should be different from the scenario
in which they make independent choices on adoption: a hospital’s adoption of L2 EMR could be
deterred either because there are enough L2 adopters in the market and the benefits of adoption
are small, or because the hospital realizes that its future benefits from adoption would decrease
as more hospitals adopt the technology.8 If the competitive effects are found to deter adoption
significantly, this could create an important source of market failure. Moreover, the hospital may
have the preemptive motive to adopt early: its adoption would inhibit the others from adopting by
decreasing their potential benefits, and this would allow the hospital to gain monopolist’s rent for a
longer period.9 If the competitive effects are substantial, the hospital would gain from preemption
and adopt earlier than in the scenario in which its rivals do not respond to its adoption. It is
interesting to examine whether the preemption exists in the adoption process.10
Competitive effects are also crucial for evaluating the effectiveness of the subsidy policy. In
2009, the American Recovery and Reinvestment Act established the Medicare/Medicaid incentive
program to subsidize the adoption of EMR.11 The subsidy lowers every potential adopter’s adoption
costs. If there is a strong competitive effect, a potential adopter has to balance the lower adoption
costs and the lower adoption benefits due to enhanced competition, and consequently would be less
likely to adopt EMR compared to the case of no competition. Thus, by overlooking competitive
effects, policy-makers may over-estimate the effectiveness of the policy.
The second objective of my paper is to evaluate the effectiveness and design of this subsidy
policy. Previous studies evaluating this policy are based mainly on statistical results or reduced-
form regressions (see Adler-Milstein et al., 2013; DesRoches et al., 2013; Dranove et al., 2015; Adler-
Milstein and Jha, 2017). The primary challenge in assessing the policy is to accurately predict the
counterfactual situation. It is difficult to tell from the data whether hospitals adopted EMR in
orders for more than 30% of patients taking medications.8An early theoretical model of technology adoption is from Reinganum (1981), who predicts that the effect of
increasing the number of firms upon the equilibrium adoption schedule is ambiguous: on the one hand, firms mayadopt early to gain a competitive advantage; on the other, each firm will capture less of the post-adoption marketand may have less incentive to adopt.
9Fudenberg and Tirole (1985) define the “preemptive adoption” as “firms will adopt sooner than they wouldchoose to were their rivals’ adoption dates fixed”, and “firms adopt preemptively to prevent or delay adoption bytheir opponents”.
10For example, Schmidt-Dengler (2006) quantifies the preemption effect in hospitals’ adoption of nuclear magneticresonance imaging, and finds the effect is small.
11As former U.S. president Barack Obama stated in a speech in 2009, “We will update and computerize ourhealthcare system to cut red tape, prevent medical mistakes, and help reduce healthcare costs by billions of dollarseach year.”
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response to the policy, or would have done so even with no subsidy.12 The dynamic structural
model developed and estimated in my paper allows me to perform counterfactual experiments to
evaluate the effectiveness of this subsidy policy. Furthermore, I explore alternative design options
of the policy to examine if the adoption could be further accelerated. Doing so sheds light on
future design of the subsidy policy that is often used by governments as a way to encourage entry,
particularly in health industries.13
For these purposes, I conduct my estimation in two steps by using U.S. hospitals’ adoption
decisions from 1999 to 2008. The first step is to examine the drivers of EMR adoption through
reduced-from regressions, and to find evidence of competitive effects. The second step is to develop
and estimate a dynamic structural model that takes hospitals’ strategic interactions into account.
In the first step, I perform a set of flexible reduced-form regressions to study how hospitals make
decisions about adoption, and which level to adopt. More importantly, I examine whether hospi-
tals’ adoption probability is negatively affected by neighboring hospitals’ adoption. Empirically,
the primary challenge regarding the estimation is to control for unobserved market heterogeneity.14
Hospitals’ choices could be correlated as a result of unobserved market factors, such as local pref-
erence for EMR and local cost advantages.15 I follow a method similar to Lin (2015) to construct
market-level group dummies that indicate different levels of profitability from EMR adoption, and
then use them to control for unobserved market heterogeneity to some extent.16 However, other
omitted market-level factors that are persistent over time may still make hospitals’ choices corre-
lated and cause bias in the estimation. To address this concern, I use an instrument method similar
to Jin (2005). A valid instrument here needs to be correlated with hospitals’ adoption decisions,
but uncorrelated with omitted local demand (or cost) factors. Consider hospitals that have the
same owners or belong to the same system but serve different geographical markets. Their choices
12As Adler-Milstein et al. (2013) put it, “ We were unable to definitively differentiate which hospitals adoptedEHRs or achieved meaningful use specifically in response to the incentives, and which hospitals had already done soor would have done so without the incentives.”
13For example, the US Health Resource and Services Administration has subsidized the entry costs of primarycare physicians, dentists, and mental health professionals that locate in Health Professional Shortage Areas (Dunneet al., 2013).
14The method to include market fixed effects is infeasible for probit and logit models, as a result of the incidentalparameters problem in a nonlinear panel data model.
15Rysman et al. (2019) find that in the case of Leadership in Energy & Environmental Design Certification,unobserved market characteristics make buildings’ choices of certification level correlated, and their differentiationstrategies difficult to identify.
16This concept to construct market (or firm) group dummies, is often used in the previous literature; see Collard-Wexler (2013) and Fan and Xiao (2015).
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are correlated because of similar organizational features or similar adoption costs, while they also
respond to local unobservables that are independent across markets. I hence use hospital A’s sister
(or system) hospital B’s adoption choices (where hospital B is located in another market) as the
instrumental variable (IV) for hospital A’s choices.17 With these empirical strategies, I find con-
sistent evidence for the presence of competitive effects and hospitals’ incentive to differentiate: the
probability of adopting L1 (L2) would decrease with more L1 (L2) adopters in the market.
I then develop a dynamic structural model of this multilevel technology adoption, based on the
framework of Ericson and Pakes (1995).18 The model takes the strategic interaction of forward-
looking hospitals into account. Hospitals are assumed to possess private information and make
adoption decisions by maximizing their discounted present value of payoffs. I estimate this model
and recover the profit and cost parameters by applying a two-stage method similar to Bajari et al.
(2007) (BBL).19 In the first stage, I estimate the policy functions and the evolution of states, which
are characterized by flexible reduced-form regressions. In the second stage, I forward-simulate the
conditional value functions and recover the profit and cost parameters by maximizing the predicted
probabilities of the observed actions, which is similar to the pseudo-maximum-likelihood estimators
introduced by Aguirregabiria and Mira (2002). Again, the presence of competitive effects is found in
the multilevel adoption process: the profits from L1 adoption decline substantially over the number
of hospitals that installed L1 only, and the profits from L2 adoption decrease greatly as more
hospitals installed L2. Hospitals of the same adoption level compete more strongly than hospitals
with different levels, and they use EMR adoption as a source of vertical product differentiation.
Based on the estimated structural parameters and the Pakes and McGuire (1994) algorithm, I
solve the finite-state equilibrium outcomes and simulate hospitals’ adoption behavior, to perform the
counterfactual experiments. My first set of experiments examines the importance of competitive
effects in the adoption process. By comparing the scenario in which hospitals make adoption
decisions with competitive effects in a duopoly market to the scenario in which hospitals make
independent choices as if they were in a monopoly market, I find that the competitive effects
on EMR adoption are substantial: it would take a longer time for hospitals in a competitive
17The empirical strategies are discussed in detail in Section 4.1.18The Ericson and Pakes (1995) framework has been used widely to study the dynamics in healthcare industry
(see Gowrisankaran and Town, 1997; Dunne et al., 2013; Lin, 2015).19Several papers apply the BBL method to study regulation in a model where firms make entry and exit decisions,
including Ryan (2012) and Suzuki (2013).
5
environment to adopt L2 EMR, especially for the later adopter in a duopoly market. Previous
studies show that EMR adoption could be deterred by adoption costs (DesRoches et al., 2008)
or concerns about patients’ privacy (Miller and Tucker, 2009), but typically overlook competitive
effects, which also play a very important role in hindering adoption. Then I examine whether the
preemption exists in the duopoly market, by performing a counterfactual experiment that removes
the preemptive motive. Similar to the method of Igami (2017), I assume hospital A in the duopoly
market does not respond to the other hospital B’s adoption, so that hospital B does not have the
preemptive motive. I focus on how hospital B would behave differently from the case with strategic
interactions. I find no evidence of preemption, and it may imply that the competitive effects are
not large enough for hospitals to gain from preemption.
My second set of experiments evaluates the subsidy-based Medicare/Medicaid incentive pro-
grams announced in 2009. Generally, eligible hospitals could begin receiving annual payments from
these programs in any year from 2011 to 2015, for a consecutive four-year period. I first analyze to
what extent the policy spurs the adoption, given that hospitals and markets are heterogeneous. I
find that large hospitals would be affected less than small hospitals given the same level of subsidy,
and would be more likely to have adopted before 2015 even with no subsidy. The current policy
also overlooks market heterogeneity. My study shows that hospitals in a small market have less
incentive to adopt, and would still lag behind even with the subsidies. As a result, a policy strat-
egy capturing hospital and market heterogeneities is a more efficient method to ensure nationwide
adoption.
Second, I explore alternative design of the policy to assess whether EMR adoption could be
further accelerated. For example, it is interesting to examine the case if the subsidy plans had been
announced earlier than 2009, as policies promoting nationwide adoption had undergone years of
bipartisan support and broad consensus since 2004.20 In a dynamic environment, hospitals’ adop-
tion probability would rise immediately after the announcement of the policy, as their option value
of adopting would increase by receiving subsidies at some time in the future. My counterfactual
results confirm the expectation. Particularly, hospitals would generally have adopted L2 EMR half
a year earlier, had the policy been passed in 2007. Thus, by speeding up the policy-making process
20The discussion of EMR adoption became important since 2004, when former U.S. president George Bush estab-lished the Office of the National Coordinator, which is tasked with the development and implementation of a strategicplan to guide the nationwide implementation of health IT (Lee et al., 2013).
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or announcing the policy earlier, adoption would be further accelerated.21
Finally, I study the role that competition plays in the effectiveness of the incentive plans.
I find that by ignoring competitive effects during the adoption process, the effectiveness of the
subsidy policy may be over-predicted. When competitive effects are taken into account, the policy
would still spur adoption significantly, but hospitals would lag behind relative to the case without
competition.
The presence of competition and differentiation in EMR adoption could challenge the intuition
that hospitals’ adoption of EMR stimulates rivals’ adoption, as a result of network externalities.
Network externalities have been found to affect technology adoption in previous studies, including
Gowrisankaran and Stavins (2004) and Tucker (2008). EMR technology exhibits network external-
ities through its feature of information exchange. However, whether network externalities actually
affect hospitals’ adoption remains unresolved in the literature. Miller and Tucker (2009) study the
effects of state privacy regulation on the adoption of enterprise EMR and find that the suppression
of network externalities would inhibit adoption. Miller and Tucker (2014) empirically find that
larger hospital systems are more likely to exchange electronic patient information internally but
are less likely to exchange patient information externally with other hospitals. Lee et al. (2013) find
no evidence of meaningful network externalities in hospitals’ EMR investments, and point out that
“only 14% of California hospitals electronically exchange medical record information with compet-
ing hospitals” based on a 2007 AHA annual survey. Freedman et al. (2018a) and Lin (2019a) point
out that EMR from different vendors typically are not interoperable. My findings of competitive
effects in the adoption suggest that either the network externalities are dominated by competitive
effects, or that hospitals do not take network externalities into account as no communication ac-
tually occurred in the early period of adoption.22 As pointed by Daniel Chavez, executive director
of the San Diego Regional Healthcare Information Exchange, “Providers all have vested interests
in health IT to improve care and optimize workflows, and all need to participate in efforts like
HIEs (Health Information Exchange) to achieve their business goals. But using the same tools,
even shared tools, is a way for hospitals as organizations to remain highly competitive rather than
21It is also related to the “ossification” problem in the law literature, which refers to the procedural constraintsimposed on federal agencies and makes the federal regulatory process burdensome and inefficient (McGarity, 1992;Mashaw, 1994).
22This paper does not separately measure the competitive effect and the network effect if any. It finds that thecompetitive effect plays a greater role and quantifies only the net effect.
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become more collaborative.”23
Recent studies also examine hospitals’ choices for EMR vendors conditional on adoption and find
evidence of network externalities. On one hand, by choosing the same vendor, hospitals enjoy a local
cost advantage (for example, through knowledge spillovers) and the possibility of communicating
better with neighboring hospitals. On the other hand, competitive effects give hospitals incentives
to differentiate over the vendor choices, and “lock-in” their patients by not sharing the information.
Freedman et al. (2018a) find that hospitals tend to agglomerate on the choices of EMR vendors
using the cross-sectional data on adoption from 2005 and 2012. Lin (2019a) reaches similar results
by studying stand-alone hospitals’ adoption from 2006 to 2009, and finds that hospitals’ profit
increases with the prevalence of a vendor in the market.24 Relative to their papers, my study
includes the early adoption stage by studying hospitals’ adoption decisions from 1999 to 2008.
More importantly, their works focus on examining whether there is horizontal differentiation or
coordination/agglomeration in the choices of EMR vendors, whereas I emphasize vertical product
differentiation along EMR adoption levels. Their results do not conflict with mine. In practice,
hospitals could be differentiated along EMR adoption levels, and at the same time, they may tend
to coordinate with each other (based on results of Freedman et al., 2018a; Lin, 2019a) by choosing
the same vendor conditional on adoption.
The remainder of the paper is structured as follows. Section 2 explains various EMR technolo-
gies. Section 3 describes the data and Section 4 presents reduced-form evidence on the adoption
process. Section 5 specifies the dynamic structural model, and Section 6 explains the estimation
method. Section 7 presents and interprets the empirical results. Section 8 describes the counter-
factual experiments, and Section 9 concludes.
2 EMR Technologies
EMR technologies refer to a wide range of information technologies used by hospitals to collect,
store and display patient information, help physicians make decisions, and coordinate healthcare.
23This is from the article “Health IT’s Effect on Inter-Hospital Competition” written by Helen Greggin 2014. https://www.beckershospitalreview.com/healthcare-information-technology/health-it-s-effect-on-inter-hospital-competition.html, accessed June 20, 2019.
24Another related paper Lin (2019b) finds that affiliated hospitals behave differently from stand-alone hospitals.Affiliated hospitals deviate from the local market-leading vendor (which has the highest local market share) andwould be more likely to choose their system-dominant vendor (which most member hospitals adopt).
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The key applications include enterprise EMR, order entry (OE), clinical data repository (CDR),
clinical decision support (CDS), computerized practitioner order entry (CPOE), and physician
documentation (PD).
Enterprise EMR is a basic EMR system that underlies other potential add-ins such as clinical
decision support, clinical data repository, and order entry (Miller and Tucker, 2009); OE pro-
vides electronic forms to streamline hospital operations, for instance, by replacing paper and faxes
(Dranove et al., 2014); CDR is a hospital’s real-time database of patients’ information, such as
test results, patient demographics, and discharge summaries; CDS supports clinicians’ decisions
by providing treatment plans; CPOE is a more advanced and sophisticated application—other
than providing patient information and clinical guidelines, it also alerts the physician to potential
errors in medication orders and potential adverse drug reactions; PD is also an advanced applica-
tion that helps physicians coordinate care by providing structured templates for entering patients’
information that is meaningful for other practitioners.
Among these applications, enterprise EMR, OE, CDR and CDS are the basic ones; they are
relatively easy to install and implement. They mainly collect, store, and display patients’ infor-
mation and are the foundation for the advanced EMR functionalities. However, the basic EMR
technologies lack advanced functionalities such as effective decision support (e.g., alerting about
potential adverse drug reactions), and easy care coordination (e.g., providing structured templates
for clinical documentation).
CPOE and PD are the advanced EMR technologies, and could help physicians make effective
use of the electronic patient data stored in basic EMR technologies. They improve healthcare qual-
ity by providing more effective physician support and smoother coordination between practitioners.
McCullough et al. (2016) find the adoption of health IT, such as CPOE, could significantly reduce
mortality for high-risk patients. Freedman et al. (2018b) find evidence that CPOE reduces the like-
lihood of adverse patient safety events, particularly for less complex patients. They attribute the
mechanism driving the findings to the decision support functionality of the advanced EMR tech-
nologies. Relative to CPOE, PD improves healthcare quality through a different channel: it enables
physicians to document and communicate patient information clearly, and thus, its functionality
mainly focuses on communication and care coordination between multiple providers (Freedman
et al., 2018b). McCullough et al. (2016) find that health IT improves quality by facilitating coor-
9
dination and communication across providers, which is more important for high-risk patients than
for low-risk ones.
The installation and implementation of advanced EMR technologies are much more costly than
that of basic EMR technologies. Hospitals need to spend an average of $80, 000 to $100, 000 per
bed for the required project planning, software, hardware, implementation, and training (Laflamme
et al., 2010). Dranove et al. (2015) point out that these costs could reach $10 million or much higher,
for an average-sized hospital.
Hence, I define the basic EMR technologies (enterprise EMR, OE, CDR and CDS) as Level 1
(L1) applications, and the advanced EMR technologies (CPOE and PD) as Level 2 (L2) applications
in my paper. This categorization is consistent with the previous literature (see Dranove et al., 2014;
Miller and Tucker, 2009; Lee et al., 2013; McCullough et al., 2016).25, 26
3 Data
I combine data on EMR adoption and data on markets to create a panel dataset of hospitals’
adoption decisions and hospital and market characteristics.
3.1 EMR Data
The data on EMR adoption and hospital characteristics are from Healthcare Information and
Management Systems Society (HIMSS) Analytics Database. The data have been widely used to
study EMR diffusion, including Hillestad, et al. (2005), Miller and Tucker (2009), Dranove et al.
(2014), Dranove et al. (2015), McCullough et al. (2016), and Freedman et al. (2018b).
HIMSS data contain information about hospitals’ address, number of beds, and the contract
time for various EMR applications if installed.27 These EMR technologies include the L1 applica-
tions of enterprise EMR, OE, CDR and CDS, and L2 applications of CPOE and PD. Furthermore,
I denote the adoption of any L1 applications as L1 adoption, and the adoption of any of the L2
25Dranove et al. (2014) define a hospital as having basic EMR applications if it has adopted OE, CDR, or CDS.The hospital has advanced EMR if it has adopted either CPOE or PD; Miller and Tucker (2009) describe enterpriseEMR as a basic EMR system that underlies other potential add-ins, such as CDS, CDR, and OE. Lee et al. (2013)and McCullough et al. (2016) define enterprise EMR as the basic application, as in Miller and Tucker (2009), andCPOE as the sophisticated EMR application.
26An alternative definition of the levels is examined as a robustness check in Section 4.3.27The contract time in the dataset is the year when a hospital first entered a contract with the EMR vendor.
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EMR as L2 adoption. A hospital is defined as a potential adopter (also Level 0 or L0) if it has
not adopted any EMR applications, as a Level 1 adopter if it has adopted only Level 1 (not yet
Level 2), and as a Level 2 adopter if it has adopted both levels. The adoption time for each level
is defined as the contract year when the hospital first enters a contract of any application of this
level.28
I use HIMSS’s annual data from 2006 to 2008 to collect each hospital’s adoption time for each
level if adopted, and create a panel dataset about hospitals’ adoption status and decisions from
1999 to 2008.29 For example, if a hospital decides to adopt L1 (and enters a contract for any L1
application) in 2002, and upgrades to L2 by signing a contract for any L2 application in 2005, it
would be a potential adopter from 1999 to 2002, an L1 adopter from 2003 to 2005, and an L2
adopter from 2006 to 2008. The installation process usually takes time: I assume in my model that
it takes 1 year for a typical hospital from entering the contract to the EMR actually being installed.
For a robustness check, as discussed in Section 4.3, I relax this assumption by assuming that the
adoption process takes 2 years, and the results do not change . I focus on adoption decisions after
1999, since the adoption rate was quite low before that.30 My sample period covers the crucially
early stage of the adoption process, prior to the announcement of the government’s EMR incentive
plan in 2009. Hence, I create the variables “number of L1 adopters” and “number of L2 adopters”
in each market each year. These are the key variables of interest, as they capture the competition
for each adoption level.
3.2 Market Definition, Market Characteristics and Sample Selection
The market is defined according to the Health Service Area (HSA) measure, developed by Makuc
et al. (1991). The HSA is a self-contained geographic region with respect to healthcare service. It
usually consists of 3 – 4 counties.31 I apply this market measure to the HIMSS adoption data, and
obtain 793 HSA markets. The markets in my data cover over 95% of the HSA markets in the U.S.
Annual market characteristics from 1999 to 2008 are mainly from Area Resource Files (ARF).
28Previous studies about EMR adoption also identify the date of adoption based on the contract date (see, e.g.,Dranove et al., 2014).
29I use data from 2006 to 2008 instead of 2008 only, in case hospitals report the information about the contractyear in 2006 or 2007, but not 2008.
30The adoption rate of L2 was less than 5% before 1999.31Other studies have used this method to define markets, including Miller and Tucker (2009).
11
The ARF provide county-level information on demographic, environmental and health resource
variables. Some sources for ARF include the American Hospital Association and the U.S. Census
Bureau. I use the variable “total hospital admissions” to approximate healthcare demand in each
market. Although each hospital’s admissions in the market may be affected by the EMR adoption
pattern in the market, as patients may flow to hospitals with EMR, total market-level admissions
are not affected and are considered exogenous.
The EMR incentive program announced in 2009 subsidizes EMR adoption as an increasing
function of the number of inpatients covered by Medicare/Medicaid. Moreover, health IT is likely
to be more effective among relatively low-income populations (Miller and Tucker, 2011), which
could be a potential motivation for adoption by hospitals in a market with more people in poverty.
To examine and control these factors, I draw the variables “number of persons eligible for Medicare”
and “percent of persons in poverty” from the ARF. All the ARF variables are aggregated at the
HSA level.
Furthermore, to control for the effect of the market’s competition level on EMR adoption, I use
the data on each hospital’s total discharges from the Healthcare Cost Report Information System
(HCRIS) to construct the market share and then the HHI (Herfindahl-Hirschman index) for each
HSA market from 1999 to 2008.32,33 Relative to the variables of number of L1/L2 adopters, which
capture the competition level for EMR adoption, the HHI variable represents the competition (or
concentration) level in the hospital market. They may have different impacts on EMR adoption.34
I restrict my sample to markets with fewer than six hospitals to focus on competition in
oligopolistic markets. There are 530 such markets, which account for 67% of the markets in the
whole dataset. Previous empirical studies show that there is little competitive effect as the sixth
entrant enters healthcare markets. For example, Abraham et al. (2007) study entry and competi-
tion in local hospital markets and find that most of the entry effects come from having a second and
32Medicare-certified institutional providers are required to submit an annual cost report to a Medicare Admin-istrative Contractor. The cost report contains provider information such as facility characteristics, utilization data,cost, and charges by cost center. The Centers for Medicare & Medicaid Services maintain the cost report data inHCRIS.
33One concern is that the HHI variable might be endogenous, as hospitals use the adoption of EMR as a competitivestrategy to attract patients. However, the demand shift affected by EMR adoption is not large enough to affect themarket concentration captured by HHI. Thus, the HHI variable is considered exogenous here. Alternatively, I use“the number of hospitals” in each market to control for its competition level, and the results are similar.
34For example, Karaca-Mandic et al. (2017) find that the medical technology of drug-eluting stents diffused fasterin markets where cardiology practices faced more competition, but the structure of the hospital market did notmatter.
12
a third hospital enter the market. The entry of a fourth hospital has little additional effect.35 Lin
(2015) also finds that for the nursing home market, the fifth and the sixth competitors have minimal
competitive impacts. Although I consider the restricted sample for most of the results, it would
nonetheless be interesting to examine the whole sample, and I include this as a robustness check
in Section 4.3. As expected, the magnitude of estimated competitive effects for EMR adoption is
much smaller for the whole sample.
As a result, I create a panel data set covering 1,535 hospitals’ adoption status and decisions
from 1999 to 2008 in 530 HSA markets. Table 1 reports the summary statistics for 2008.
Table 1: Summary Statistics
Variable Obs. Mean Std. Dev.
Number of beds in the hospital 1,535 99.016 113.52HHI (Herfindahl-Hirschman Index) 530 0.59 0.24Total hospital admissions in the market(1000) 530 13.86 17.36Number of persons eligible for Medicare in the market(1000) 530 21.12 21.87Percent of persons in poverty in the market 530 15.92 5.46
Time 2008
Figure 1 shows the adoption rates of Level 1 and Level 2 EMR applications over the sample
period. The adoption rate of L1 EMR started from 38.6%, meaning that 592 of the 1,535 hospitals
had adopted L1 by 1999. This rate increased steadily to 69.8% (approximately 1,071 hospitals) in
2008, showing that L1 EMR were widely adopted by the end of the sample period. The adoption
rate of L2 EMR is much smaller. It increased from a very low value of 5.4% (83 hospitals) in 1999
to 28.9% (443 hospitals) in 2008. Hazard rates of each adoption level are presented in Figure 2,
showing the adoption decisions for hospitals at different levels over time. The hazard rate from L0
to L1 is the ratio of the number of potential adopters that decide to adopt only L1 applications,
to the total number of potential adopters each year. The hazard rate from L0 to L2 is the ratio of
the number of potential adopters that decide to adopt Level 2 applications, to the total number of
potential adopters each year. Similarly, the hazard rate from L1 to L2 is defined as the rate of L1
adopters that decide to upgrade to L2. From the figure, the hazard rate from L0 to L1 is slightly
higher than the other two, indicating a relatively stronger incentive to adopt L1 applications. These
35Their method is based on the classic paper by Bresnahan and Reiss (1991), which finds that once the markethas between three and five firms, the next entrant has little effect on competitive conduct.
13
three hazard rates generally increased from the beginning of the sample period, and fell after 2005.
Notably, the hazard rate from L1 to L2 dropped substantially from 2006. This may suggest that,
as hospitals with higher incentives had already adopted EMR in the early stage, adoption began
to slow down because the remaining hospitals had various concerns, such as substantial costs,
patients’ privacy, and uncertainty about return on investment. These concerns may be particularly
important for L1 adopters.
Figure 1: Adoption Rate of L1&L2 Applications
010
2030
4050
6070
80Ad
optio
n R
ate
(%)
1999 2000 2001 2002 2003 2004 2005 2006 2007 2008year
L1 application L2 application
Figure 2: Hazard Rate
02
46
810
12H
azar
d R
ate
(%)
1999 2000 2001 2002 2003 2004 2005 2006 2007 2008year
From potential adopter to L1 adopterFrom potential adopter to L2 adopterfrom L1 adopter to L2 adopter
4 Reduced-form Results: Hospitals’ Adoption Decisions
As an initial piece of evidence on the drivers of adoption decisions, I examine how hospitals make
decisions through reduced-form regressions. The results are be used as the policy functions during
the estimation of the dynamic structural model in the next section.
4.1 Level 1 Adopters
Active hospitals include Level 1 adopters and potential adopters. I first examine the behavior of
Level 1 adopters. Level 1 adopters make decisions about whether to upgrade to Level 2. I estimate
the following model:
Pr(Yit = 1|wit) = F (w′itλw) (4.1)
14
where variable Yit = 0 if Level 1 adopter i does not upgrade at time t, and Yit = 1 if it upgrades
to Level 2. F (·) is a known function. The vector wit consists of the constant term, and a set
of variables that might affect the adoption decision, including the number of Level 1 adopters
and Level 2 adopters in the market, other observed market characteristics (HHI, total hospital
admissions, number of persons eligible for Medicare, and percent of persons in poverty), observed
hospital characteristics (number of beds), and market and year fixed effects. The specifications
considered here include a linear probability model, a probit model, a logit Model, and an IV probit
model.
I first estimate a linear probability model by OLS with market fixed effects. In this case,
F (w′itλw) = w′itλw. Table 2 Specification I shows the results from this OLS regression. The
coefficient on “number of Level 2 adopters in each market” is negative and significant, indicating
the presence of differentiation: Level 1 adopters are more likely to stay at Level 1 and not upgrade,
if there are more Level 2 hospitals. The coefficients on year dummies increase over time, showing
a time trend for EMR adoption. The possible explanations are that adoption costs are falling,
revenues from EMR use are climbing, or people are favoring this technology more.
I then estimate a probit model and a logit model without market fixed effects. In the case of
a probit model, F (·) is a cumulative distribution function (cdf) of standard normal distribution,
and F (·) is a cdf of logistic distribution in the case of a logit model. The market fixed effects are
infeasible for probit and logit models, owing to the incidental parameters problem in the nonlinear
panel data model. Specification II shows the results. The results from Specifications I and II
are quite different: for example, the significantly negative coefficient on “Number of L2 adopters”
becomes insignificant. This could be the result of different model specifications36, or the lack of
market fixed effects in Specification II. In any case, it is necessary to include unobserved market
heterogeneity in the model: unobserved market heterogeneity in profitability for Level 1 and Level
2 adoption would greatly affect adoption behavior, as profitable markets tend to support more
adopters.
To control unobserved market heterogeneity, I follow a method similar to Lin (2015). The idea
is to construct market-level group dummies that indicate different levels of profitability from L1
36The linear probability model has a number of shortcomings. For instance, it often produces nonsense predictedprobabilities.
15
and L2 adoption, based on the results of regressions with market fixed effects. This allows hospitals
to have more incentives to adopt if they are in a market with a high level of profitability. This
concept to construct market (or firm) group dummies that capture the unobserved heterogeneity
persistent over time, is often used in the previous literature. For example, Collard-Wexler (2013)
constructs so-called market-category effects based on the average number of plants in a market
across time. Fan and Xiao (2015) use a similar method to categorize firms into two groups, one
with low entry cost, and the other with high entry cost, based on a logit model that explains firms’
entry decisions.
Specifically, I first run two regressions with the market fixed effects. The regressions regress
the number of Level 1 and Level 2 adopters in each market respectively, on observed market
characteristics (i.e., HHI, total hospital admissions, and number of persons eligible for Medicare
in each market) and market and year fixed effects. The first regression provides the market fixed
effects for profitability from Level 1 adoption, while the second one gives the market fixed effects
for Level 2 adoption. I then compute the 10th, 20th, ..., 90th percentiles for the estimated market
fixed effects of each level. Accordingly, each market is assigned by 18 group dummies: The first
nine dummies indicate which percentile range the market is in for L1 adoption, and the second nine
dummies indicate which percentile range it is in for L2 adoption. If a market is above the 90th
percentile for both L1 and L2 adoption, it is categorized as one of the most profitable markets to
adopt EMR. Following Collard-Wexler (2013), I refer to these dummies as market-category effects.
I perform the probit and logit regressions for Level 1 adopters again, but this time controlling
for the market-category effects. The results are reported in Table 2 Specification III. Relative to
Specification II, both pseudo R-squared and log pseudo likelihood improve noticeably in Specifica-
tion III, which allows the model to better fit the data. Similar to Specification I, the coefficient on
the number of L2 adopters is significantly negative. Moreover, the coefficient on the number of L1
adopters is positive and precisely estimated. The results indicate the presence of differentiation in
the adoption process. Level 1 adopters are more likely to upgrade if there are more Level 1 adopters
or fewer Level 2 adopters. By computing the average marginal effects for the logit regression, one
more L1 adopter in the market would increase the probability of upgrading by 1.5%, while one
more L2 adopter would decrease this probability by 4.1%. The probit model gives the exact same
marginal effect of the number of L1 adopters (1.5%), and a very similar effect of the number of L2
16
adopters (3.9%).
Even if unobserved market heterogeneity in profitability from L1 and L2 adoption is controlled
to some extent, other omitted market-level factors that are persistent over time might still cause bias
in the estimation. As a result, adoption decisions may be correlated among hospitals. To address
this concern, I use the instrument method similar to Jin (2005). A valid instrument here needs to
be correlated with neighboring hospitals’ adoption decisions, but uncorrelated with omitted local
demand (or cost) factors.
Consider hospitals that have the same owners or belong to the same system, but serve different
geographical markets (I refer to these hospitals as “sisters”). On the one hand, sister hospitals have
correlated adoption decisions, because they always share similar organizational features, require
similar service quality and have similar technology adoption costs.37 On the other hand, as they
serve different markets, they also respond to omitted local factors when making adoption decisions,
and these omitted local factors are assumed independent across markets.38 Thus, for hospital i’s
adoption in market A, its sister j’s adoption behavior in another market B is a valid IV: They
have correlated adoption behavior as sisters, and hospital j’s adoption behavior does not respond
to unobserved local factors in market A.
Thus, I construct the instruments for the endogenous variables “number of Level 1 adopters”
and “number of Level 2 adopters.” The exact calculation proceeds as follows. I first create two
dummies, L1 and L2, for each hospital, indicating whether it is an L1 adopter and whether it is
an L2 adopter. I then identify the hospital’s sisters in other markets and construct the variable
IV L1, as the mean of dummies L1 of its sisters in other markets, and similarly construct IV L2
as the mean of dummies L2. The instruments IV n1 for “number of Level 1 adopters” and IV n2
for “number of Level 2 adopters” are obtained from summing IV L1 and IV L2 for the hospitals
in each market respectively. Stand-alone hospitals do not have sisters and cannot contribute to the
construction of the instruments. Therefore, I create the variable “proportion of sister hospitals,”
defined as the ratio of the number of hospitals with sisters in other markets to the number of all
hospitals in the market. This variable has a mean of 0.33 and a standard deviation of 0.32. Because
37Regarding EMR adoption, sister hospitals could share a licensing fee, human-capital training material, and costsfor external consultants, etc (Lin, 2019b).
38Jin (2005) makes similar assumptions in the context of health maintenance organizations’ voluntary disclosureof product quality.
17
Table 2: Adoption for Level 1 Adopters
I II III IV
OLS Probit Logit Probit Logit IV Probit
Number of L1 adopters 0.004 0.068* 0.146* 0.23*** 0.481*** 0.461(0.008) (0.041) (0.088) (0.065) (0.140) (0.344)
Number of L2 adopters -0.051*** -0.053 -0.125 -0.593*** -1.314*** -0.52*(0.011) (0.056) (0.124) (0.104) (0.228) (0.305)
Log of number of beds 0.006 0.069** 0.155** 0.120*** 0.262*** 0.08(0.004) (0.034) (0.077) (0.041) (0.087) (0.055)
HHI 0.032 0.16 0.339 0.070 0.136 0.229(0.038) (0.187) (0.420) (0.193) (0.415) (0.315)
Log of total admissions 0.173** -0.021 0 0.709*** 1.568*** 0.701**(0.068) (0.154) (0.348) (0.200) (0.443) (0.282)
Log of number of persons 0.098 0.099 0.196 1.427*** 3.027*** 1.274***eligible for Medicare (0.091) (0.100) (0.226) (0.159) (0.323) (0.308)Percent of persons in -0.156 -2.419*** -5.498*** 0.654 1.325 0.160poverty (0.299) (0.770) (1.786) (0.793) (1.811) (1.287)Year 2000 dummy 0.004 0.305 0.836 0.252 0.670 0.152
(0.005) (0.261) (0.764) (0.327) (0.808) (0.496)Year 2001 dummy 0.012 0.599** 1.597* 0.587 1.509 0.490
(0.009) (0.292) (0.823) (0.391) (0.922) (0.456)Year 2002 dummy 0.027*** 0.767*** 1.989*** 1.030*** 2.308*** 0.941**
(0.009) (0.269) (0.763) (0.369) (0.887) (0.444)Year 2003 dummy 0.042*** 0.958*** 2.428*** 1.262*** 2.956*** 1.298***
(0.013) (0.269) (0.758) (0.371) (0.881) (0.445)Year 2004 dummy 0.065*** 1.102*** 2.740*** 1.565*** 3.727*** 1.587***
(0.013) (0.261) (0.741) (0.373) (0.886) (0.456)Year 2005 dummy 0.087*** 1.203*** 2.989*** 1.789*** 4.149*** 1.628***
(0.017) (0.262) (0.742) (0.373) (0.881) (0.463)Year 2006 dummy 0.098*** 1.247*** 3.053*** 1.871*** 4.313*** 1.830***
(0.017) (0.260) (0.739) (0.377) (0.893) (0.481)Year 2007 dummy 0.08*** 1.04*** 2.61*** 1.679*** 3.883*** 1.662***
(0.016) (0.264) (0.748) (0.379) (0.896) (0.499)Year 2008 dummy 0.074*** 0.900*** 2.274*** 1.513*** 3.483*** 1.576***
(0.016) (0.269) (0.760) (0.385) (0.911) (0.512)Proportion of sister 0.335hospitals (0.204)Market-category effects No No No Yes Yes YesMarket fixed effects Yes No No No No NoObs. used in the estimation 6162 6162 6162 6162 6162 3287(Pseudo) R-squared 0.151 0.060 0.060 0.208 0.210Log pseudo-likelihood -905 -904 -763 -760
Robust standard errors are clustered at the market level and are in parentheses. The unit of observation ishospital-year. The year dummy for 1999 is omitted in all the specifications. The results of market-categoryeffects are not reported. ∗∗∗p < .01,∗∗ p < .05,∗ p < .10.
18
“proportion of sister hospitals” is observable to local customers, I include it as a control variable
directly in the regression. Moreover, markets without any sister hospitals are not considered. As a
result, the subsample for this IV method includes 272 markets and 3,287 hospital-year observations
(compared to 6,162 observations in the full sample). To provide more support for the validity of
the instruments, I calculate that the instrument IV n1 and “number of Level 1 adopters” have a
correlation coefficient of 0.30, and the instrument IV n2 and “number of Level 2 adopters” have a
correlation coefficient as high as 0.65 in the subsample.
I then perform the two-step IV probit model developed by Newey (1987),39 taking the number
of Level 1 and Level 2 adopters as endogenous. Table 2 Specification IV shows the results. The
coefficient on “number of Level 2 adopters” is still negative and significant, indicating that there
are incentives for differentiation.
4.2 Potential Adopters
Potential adopters make decisions about whether to adopt and which level to adopt. I estimate the
following multinomial logit model:
Pr(Yit = j|wit) =exp(w′itλj)∑j exp(w′itλj)
(4.2)
where j = 0 if the potential adopter chooses not to adopt any EMR, j = 1 if the potential adopter
chooses to adopt Level 1 EMR, and j = 2 if the potential adopter adopts Level 2 EMR. The variable
wit including the constant term, the number of Level 1 adopters and Level 2 adopters in the market,
other observed market characteristics (HHI, total hospital admissions, number of persons eligible
for Medicare, and percent of persons in poverty) and hospital characteristics (number of beds),
market-category effects and year fixed effects.
The results are reported in Table 3. I find negative and significant coefficients on “number of
Level 1 adopters” and “number of Level 2 adopters” in each market for both L1 and L2 adoption.
This shows the strong competitive effects of EMR adoption. By computing the average marginal
effects, I find that one more L1 adopter would decrease the probability of adopting L1 by 7.8%,
39Newey (1987) develops a consistent two-step estimator for the probit model with endogenous regressors. Thefirst step is to regress endogenous variables on valid instruments and the other exogenous explanatory variables, andthe second step is to include the residuals from the first step in the probit model.
19
and decrease the probability of adopting L2 by 1.5%. One more L2 adopter would decrease the
probability of adopting L1 by 3.5%, and that of adopting L2 by 4.0%. This result also shows the
incentive to differentiate, as competition is more intense among hospitals of the same adoption
level. The competitive effect from L1 adopters is stronger on L1 adoption, than on L2 adoption.
Similarly, L2 adopters deter the adoption of L2 more than that of L1.
Other results are as follows. Hospitals with more beds are more likely to adopt, especially Level
2. Larger hospitals can make better use of EMR applications by facilitating internal information
exchange and coordination. Another notable result is that the increasing year effects indicate a
rising trend of EMR adoption.
4.3 Robustness Checks
In my model, one assumption is that a typical hospital takes 1 year from making the decision of
adoption to actually having EMR technologies installed. A concern is that the installation process
is complicated and may take more than 1 year in some cases. Therefore, I relax this by assuming
that it takes 2 years to install and implement EMR technologies.40 The variables “number of L1
adopters” and “number of L2 adopters” variables in the market are recalculated accordingly. I
then perform a logit regression for L1 adopters, as in Specification III in Table 2, and multinomial
logit regression for potential adopters as in Table 3. Table 4 displays the coefficients, standard
errors, and average marginal effects for the variables of interest, which are the number of L1 and
L2 adopters in the market. The results do not change much. The competitive effects and incentives
to differentiate are still very strong with this modified assumption.
I conduct a robustness check to see, whether the results of competition and differentiation hold,
with an alternative definition of levels. As described before, I define L1 adoption as the adoption
of any of the basic applications, including enterprise EMR, OE, CDR, and CDS. L2 adoption is
defined as the adoption of either CPOE or PD. Some papers focus on the adoption of CDR, and
find that hospitals tend to agglomerate on the choices of EMR vendors (e.g., Freedman et al.,
2018a; Lin, 2019a). Therefore, I change the definition of L1 adoption to CDR adoption, and retain
the definition of L2 adoption. With this new definition, I again perform the logit regression for L1
40Data from 144 hospitals suggest that implementation occurs 2.03 years on average after the contract date,according to 2007 HIMSS Analytics Database survey.
20
Table 3: Adoption for Potential Adopters
Adopt L1 Adopt L2
Number of L1 adopters -1.896*** -0.921***(0.174) (0.238)
Number of L2 adopters -0.922*** -2.079***(0.192) (0.245)
Log of number of beds 0.455*** 0.732***(0.060) (0.102)
HHI 0.597* 0.33(0.319) (0.435)
Log of total admissions 0.172 2.215***(0.394) (0.593)
Log of number of persons eligible for Medicare -0.395 2.584***(0.241) (0.380)
Percent of persons in poverty 1.645 3.978**(1.215) (1.943)
Year 2000 dummy 0.122 0.816(0.261) (0.592)
Year 2001 dummy 0.513** 2.062***(0.250) (0.596)
Year 2002 dummy 1.051*** 2.307***(0.260) (0.586)
Year 2003 dummy 1.654*** 3.446***(0.243) (0.590)
Year 2004 dummy 1.458*** 4.187***(0.284) (0.634)
Year 2005 dummy 1.848*** 4.259***(0.288) (0.677)
Year 2006 dummy 1.498*** 4.038***(0.321) (0.680)
Year 2007 dummy 1.512*** 4.263***(0.334) (0.665)
Year 2008 dummy 0.73* 3.123***(0.429) (0.807)
Market-category effects YesObs. used in estimation 6893(Pseudo) R-squared 0.186Log pseudo-likelihood -1694
Robust standard errors are clustered at the market level and are inparentheses. The unit of observation is hospital-year. The results ofmarket-category effects are not reported. ∗∗∗p < .01,∗∗ p < .05,∗ p <.10.
21
Table 4: Robustness Check: Change of Installation Time
L1 Adopters (Logit) Potential Adopters (Multinomial Logit)Upgrade to L2 Adopt L1 Adopt L2
Coef. M. E. Coef. M. E. Coef. M. E.
Number of L1 adopters 0.708*** 0.022 -1.779*** -0.074 -0.891*** -0.015(0.136) (0.160) (0.234)
Number of L2 adopters -1.379*** -0.042 -0.828*** -0.032 -1.897*** -0.037(0.220) (0.179) (0.240)
Obs. used in estimation 6162 6893
Robust standard errors are clustered at the market level and are in parentheses. Theunit of observation is hospital-year. Observed hospital and other market characteristics,market-category effects, and time dummies are not reported. ∗∗∗p < .01,∗∗ p < .05,∗ p <.10.
adopters, as in Specification III in Table 2 and multinomial logit regression for potential adopters
as in Table 3. Table 5 shows the results, which again indicate the existence of competitive effects
and the incentive to differentiate. As discussed in the Introduction, I focus on the study of adoption
levels, while Freedman et al. (2018a) and Lin (2019a) emphasize the choices of vendors conditional
on adoption. Thus, their results do not conflict with mine.
Table 5: Robustness Check: Define L1 as CDR
L1 Adopters (Logit) Potential Adopters (Multinomial Logit)Upgrade to L2 Adopt L1 Adopt L2
Coef. M. E. Coef. M. E. Coef. M. E.
Number of L1 adopters 0.957*** 0.030 -2.023*** -0.052 -0.531*** -0.009(0.134) (0.259) (0.249)
Number of L2 adopters -1.216*** -0.038 -0.443** -0.010 -1.610*** -0.032(0.246) (0.214) (0.183)
Obs. used in estimation 4122 9398
Robust standard errors are clustered at the market level and are in parentheses. Theunit of observation is hospital-year. Observed hospital and other market characteristics,market-category effects, and time dummies are not reported. ∗∗∗p < .01,∗∗ p < .05,∗ p <.10.
To focus on oligopolistic market competition, I restrict my sample to markets with fewer than
six hospitals. Although previous studies show that the competitive effects from another entry would
be dampened in markets with more firms (e.g., Bresnahan and Reiss, 1991; Abraham et al., 2007;
Lin, 2015), it is still interesting to see whether this is the case in the context of EMR adoption.
22
Therefore, I examine the whole sample with all 793 markets as a robustness check. I perform the
logit regression for L1 adopters, as in Specification III in Table 2, and multinomial logit regression
for potential adopters as in Table 3. The results are presented in Table 6. As expected, the
competitive effects are still present, but smaller, than in Specification III in Table 2, and Table 3.
Table 6: Robustness Check: All Markets
L1 Adopters (Logit) Potential Adopters (Multinomial Logit)Upgrade to L2 Adopt L1 Adopt L2
Coef. M. E. Coef. M. E. Coef. M. E.
Number of L1 adopters 0.002 0.000 -0.049** -0.002 -0.099*** -0.003(0.020) (0.025) (0.023)
Number of L2 adopters -0.179*** -0.007 0.006 0.001 -0.108*** -0.003(0.025) (0.016) (0.028)
Obs. used in estimation 20091 18991
Robust standard errors are clustered at the market level and are in parentheses. Theunit of observation is hospital-year. Observed hospital and other market characteristics,market-category effects, and time dummies are not reported. ∗∗∗p < .01,∗∗ p < .05,∗ p <.10.
5 Structural Model
To conduct the counterfactual experiments so as to further evaluate the importance of competition
and the effects of the incentive policy, I require a structural model. Hence, I develop a dynamic
structural model, capturing the competitive effects of each adoption level and the strategic inter-
action between hospitals. My model builds on the theoretical framework developed by Ericson and
Pakes (1995), which is designed to capture the evolution of an industry with heterogeneous firms.
There are three types of hospitals in my model: potential adopters, L1 adopters and L2 adopters.
The active hospitals that make adoption decisions include potential adopters and Level 1 adopters.
Time is discrete and infinite, and each decision period is 1 year. Specifically, the adoption game
is played as follows. At the beginning of each period, hospitals observe the current state realiza-
tions and their private draws from the cost distribution. Active hospitals then make simultaneous
decisions. Potential adopters decide whether, and which level, to adopt. Level 1 adopters choose
to stay at Level 1 or upgrade to Level 2. The adoption is irreversible. After all these decisions are
made, hospitals incur costs if they decide to adopt or upgrade. They receive profits based on the
23
level at the beginning of each period. Adoption affects profits from the period following adoption.
Finally, markets evolve to the next period.
The equilibrium notion used here is that of Markov perfect Nash equilibrium as defined by
Maskin and Tirole (1988), where players’ strategies are functions of current, pay-relevant state
variables and private shocks. Forward-looking hospitals make adoption decisions to maximize the
expected present discounted value of flow profits, given the strategies of the others.41
5.1 States and Actions
The state sit for hospital i in market j at time t, is captured by the following variables: 42
sit = {xit, εit}
xit = {Lit, n1jt, n2jt, hi, zjt, τ t}
where xit is the observed state, and εit is the unobserved state (hospitals’ private information). For
the observed state variables, Lit, n1jt, and n2jt are endogenously determined by the model, while
hi, zjt, and τ t are exogenous variables. The variable Lit denotes hospital i’s adoption levels: a
potential adopter is at Level 0 (L = 0), a Level 1 hospital is at Level 1 (L = 1) , and a Level 2
hospital is at Level 2 (L = 2). The variables n1jt and n2jt represent the number of Level 1 adopters
and Level 2 adopters, respectively, in market j at time t. They capture the competitive effects and
are the key variables in the model. Variable hi denotes the observed hospital characteristics, such
as the number of beds in the hospital. The number of beds is assumed not to be affected by the
adoption decisions (EMR adoption is considered a relatively small decision, and does not affect the
number of beds). Let zjt denote the observed exogenous market characteristics, including HHI,
total hospital admissions, number of persons eligible for Medicare, percent of persons in poverty,
and market-category effects. Let τ t denote the year effects of adoption, which are the coefficients
on year dummies from reduced-form regressions in Table 2 and Table 3. These year effects capture
41The introduction of private shocks associated with actions guarantees that at least one pure strategy equilibriumexists in this setting. Please see Doraszelski and Satterthwaite (2010) and Gowrisankaran (1995) for more discussionabout the existence of an equilibrium. There may be multiple equilibria. In the paper, I use the method of Bajariet al. (2007) that assumes the data are generated by a single Markov perfect Nash equilibrium profile and recoversthe equilibrium beliefs directly from the data.
42For simplicity, I use sit to denote the state for hospital i in market j at time t, instead of sijt.
24
the time trend for EMR adoption and are assumed to follow a first order autoregressive process.43
The unobserved vector εit is the idiosyncratic private cost shock associated with each action that
hospital i may take at time t, and is assumed to follow an i.i.d. Type 1 extreme value distribution.
Potential adopters and Level 1 adopters are active hospitals in the market. The action for an
active hospital i at time t is denoted by ait. Potential adopters make decisions about whether and
which level to adopt. Let ait = 0 denote the action of not adopting, ait = 1 denote the action of
adopting the first level and becoming Level 1 adopters, and ait = 2 denote the action of adopting
both levels and becoming Level 2 adopters. Level 1 adopters make decisions about whether to
upgrade to Level 2. Let ait = 1 denote the action of not upgrading, and ait = 2 denote the action
of upgrading to Level 2 and becoming Level 2 adopters.
5.2 Profit and Cost Function
Hospitals receive profits every period, conditional on the adoption of EMR.44 Let φ(s|γ) represent
the conditional per-period profit function for a hospital in state s. The functions are linear in s,
and the profit of not adopting is normalized to 0. Specifically:
φ(sit|γ) =1(Lit = 0)× 0
+ 1(Lit = 1)(γ11n1jt + γ12n2jt + γ1hhi + γ1zzjt)
+ 1(Lit = 2)(γ21n1jt + γ22n2jt + γ2hhi + γ2zzjt)
(5.1)
The functions depend on hospital i’s own characteristics and market-level characteristics.45
The externalities of adoption are captured by the key variables of n1jt and n2jt. The revenue from
adoption is expected to increase over the size of the hospital, measured by the number of beds
(hi). The market concentration, measured by HHI, potentially affects the profit functions, and it
would be interesting to quantify this effect. Total hospital admissions in the market are to proxy
the market demand for healthcare. The variables of number of persons eligible for Medicare and
43The specification of year effects is further discussed in Section 6.1.2.44In my model, I cannot separately identify the returns and maintenance costs of EMR per period after the
adoption, since they are both functions of the state variables. Thus, I assume a sunk cost at the time of adoption,and the ongoing profits per period after the adoption.
45Adopting EMR can change profits through different channels, for example, by raising revenue per patient orprocedure, raising the number of patients or procedures, or lowering operating costs. I do not distinguish betweenthese channels, and all of them are captured by to the extent that they vary with the exogenous market and hospitalcharacteristics in the profit function.
25
percent of persons in poverty capture not only the demand for healthcare but also demand for
EMR technologies, as studies show that health IT is likely to be more effective among relatively
low-income populations (Miller and Tucker, 2011). Moreover, these variables could indicate the
possible returns from the Medicare/Medicaid EMR incentive plan enacted in 2009, as subsidies are
functions of inpatients covered by Medicare/Medicaid. The market-category effects, again, capture
the unobserved market heterogeneity in profitability from L1 and L2 adoption.
The upfront adoption costs include costs for software and hardware installation, and staff train-
ing. The cost functions consist of fixed costs, variable costs associated with time, and hospitals’
private idiosyncratic shocks, which are associated with actions. Other than the private shocks,
costs are considered homogeneous for hospitals at the same time.46
Potential adopters incur costs when adopting Level 1 or Level 2, and Level 1 adopters pay the
costs to upgrade to Level 2. No cost is incurred when potential adopters choose not to adopt, or
when Level 1 adopters stay at Level 1. Specifically, the costs are as follows:
C(sit, ait|c) + εit(ait) =1(Lit = 0, ait = 0)0
+ 1(Lit = 1, ait = 1)0
+ 1(Lit = 0, ait = 1))(c10 + c1ττ1t )
+ 1(Lit = 0, ait = 2))(c20 + c2ττ2t )
+ 1(Lit = 1, ait = 2))(c21 + c12τ τ12t )
+ εit(ait),
(5.2)
where τ1t , τ2t , τ
12t capture the time effects. From the results in Tables 2 and 3, we notice that the year
effects significantly affect adoption, and there is a roughly rising trend over time. The reasons could
be that the price and functionality of EMR systems change, that governments’ policies regarding
EMR adoption develop, or simply that people’s taste for EMR changes as time goes by. To include
the time effects in the model, I allow the adoption costs to depend on year effects obtained from
the multinomial logit regression for potential adopters, and allow the upgrade costs to depend on
46Ideally, the costs should be modeled heterogeneous on observed hospital and market characteristics. However, asI have already assumed profits to be heterogeneous on observables, I cannot model heterogeneity for both post-entryprofits and entry costs. This is common for dynamic models with only entry data (see Fan and Xiao, 2015), becausewe cannot tell whether the variation of entry times is caused by heterogeneity from post-entry profits, or heterogeneityfrom entry costs.
26
the year effects from the logit regression for L1 adopters. In other words, variable τ1t consists of the
coefficients on year dummies from the first column in Table 3, variable τ2t of the coefficients on year
dummies from the second column, and variable τ12t of the coefficients on year dummies from the
logit regression in Table 2.47 As these reduced-form regressions examine the drivers of potential
adopters’ and L1 adopters’ decisions, respectively, the year effects obtained should capture the
corresponding time trend for different levels of EMR adoption.
In summary, the parameters θ to be estimated include γ in the profit functions and c in the
cost functions. Parameters γ11, γ12, γ21 and γ22 measure the competitive effects and are of great
interest in the paper.
5.3 Equilibrium
In each period, forward-looking hospitals make adoption decisions to maximize the expected present
discounted value of flow profits, given the strategies of the others. Based on the current state
variables, hospital i’s strategy at t: σit, is a mapping from state vectors to actions:
σit : sit 7→ ait
The value function for a hospital at adoption level L (L = 0, 1, 2) and in state s, is denoted by
VL(s). The Bellman equations are as follows:
V0(s) = maxa∈{0,1,2}
{βE[Va(s
′)|s]
+ φ(s)− C(s, a)− ε(a)
}(5.3)
V1(s) = maxa∈{1,2}
{βE[Va(s
′)|s]
+ φ(s)− C(s, a)− ε(a)
}(5.4)
V2(s) = φ(s) + βE[V2(s
′)|s]
(5.5)
Given the private shocks, potential adopters maximize their profits by choosing whether to adopt,
and which level to adopt, while Level 1 adopters choose whether to upgrade. Level 2 adopters
are assumed inactive, as I do not model a higher level in this paper and the adoption process is
considered irreversible.
The equilibrium is a Markov perfect Nash equilibrium (MPNE), which is defined as the strategy
47The year effects follow an AR(1) process and are discussed in Section 6.1.2.
27
σ∗ that satisfies:
V (s|σ∗i , σ∗−i) ≥ V (s|σ′i, σ∗−i)
for any σ′i, and any s.
6 Estimation
For the estimation, I apply the method of Bajari et al. (2007) (BBL), which provides a two-stage
algorithm for estimating dynamic games under the assumption that the behavior is consistent with
Markov perfect equilibrium.48 In the first stage, I estimate the policy functions and the evolution
of states, which are characterized by flexible reduced-form regressions. In the second stage, the
structural parameters are estimated by imposing the optimality conditions. Forward-looking agents
choose their actions by maximizing the expected discounted present value of profits, given their
beliefs in equilibrium. I apply the method of forward simulation to obtain the value functions
associated with different actions, then the probabilities of each action. The structural parameters
are recovered by maximizing the predicted probabilities of the observed actions, similar to a pseudo-
maximum-likelihood estimator introduced by Aguirregabiria and Mira (2002).
The BBL method alleviates computational burden, as the two-step approach does not require
equilibrium computations. Also, this method can be used to estimate models with multiple equi-
libria under the assumption that only one equilibrium is observed in the data (i.e., the same policy
function predicts behavior across markets). Because the first-step estimation recovers the agents’
correct beliefs for the equilibrium actually played in the data, there is no need for the researcher
to make assumptions about which of many potential equilibria is being played.
6.1 The First Step: Transitions between States
The first step examines the policy functions and the evolution of states. In the equilibrium actually
played in the data, agents are assumed to have correct beliefs about the environment as well as other
players’ behavior, and they make adoption decisions based on the current state vectors they face.
48It is difficult to apply the Ericson and Pakes (1995) framework to the data, because of the complexity ofcomputing an equilibrium and multiple equilibria. To ease the computational burden, a series of papers propose atwo-stage method to estimate dynamic games, including Bajari et al. (2007), Aguirregabiria and Mira (2007), Pakeset al. (2007), and Pesendorfer and Schmidt-Dengler (2008). These papers have built on the insights of Rust (1987),Hotz and Miller (1993), and Hotz et al. (1994).
28
The state variables in the next period are functions of the current state and actions. The decision-
making process and state transitions are characterized by different specifications of reduced-form
regressions.
6.1.1 Adoption Decisions of Hospitals
Active hospitals include Level 1 adopters and potential adopters. Level 1 adopters make decisions
about whether to upgrade to Level 2. I use the logit regression shown in Table 2 Specification III
as the policy function. Potential adopters make decisions about whether and which level to adopt.
I use the multinomial logit regression shown in Table 3 to capture their decisions. I choose these
regressions because they fit the data well, and the coefficients are estimated precisely. The adoption
decisions update hospitals’ status in the next period indicated by Lit, as well as the number of L1
and L2 adopters in the market, denoted by n1jt and n2jt, respectively.
6.1.2 Evolution of Exogenous Variables
The exogenous variables hi, zjt and τt include hospital characteristics (the number of beds for each
hospital), market characteristics (HHI, total hospital admissions, number of persons eligible for
Medicare, percent of persons in poverty, and market-category effects), and year effects for EMR
adoption. Hospital and market characteristics are assumed to stay fixed at the values when the
hospitals make the decisions.49 Year effects τ1t , τ2t and τ12t which affect the installation costs of
adoption, are assumed to follow an AR(1) process as follows:
τat+1 = µa0 + µaττat + ωat+1 (a = 1, 2, or 12) (6.1)
where ωat is a shock following a normal distribution, that is, ωat ∼ N(0, σa).
One concern about this AR(1) specification is that it may not capture the possible breaks of
policy, technology, or preference during the sample period. EMR adoption has become a serious
and particularly important topic since 2004, when former U.S. president Bush proposed that EMR
technologies should be widespread in the U.S. healthcare system by 2014. Moreover, he announced
several new initiatives, such as doubling funding for demonstration projects in health IT, and using
49In other words, for the forward simulation starting from period t, hospitals assume the exogenous hospital andmarket characteristics stay constant at the current values.
29
the federal government to foster the adoption of health IT. This proposition received bipartisan
support. In 2009, former U.S. president Obama signed the American Recovery and Reinvestment
Act into law, to promote the national adoption of EMR. Furthermore, regarding EMR technology,
the integrated EMR system became popular around the mid-2000s. For the preference for EMR,
people started to have concerns about patients’ privacy, and uncertainty surrounded adopters’
cost savings from EMR. To address these concerns, I consider alternative specifications to include
a policy/technology/preference break around the mid-2000s. Specifically, I create time dummies
D2003. D2004, ..., D2007 to indicate periods in or after 2003, 2004, ..., 2007 respectively. I add
these time dummies to the above AR(1) regressions one by one and find that only the coefficient
on D2006 in the AR(1) regression for τ12t is precisely estimated, and is negative in this case. This
result shows that year effects τ12t experienced a drop in 2006, suggesting that the upgrading trend
slowed down. Therefore, for the transition of τ12t , the following specification is used:
τ12t+1 = µ120 + µdD2006 + µ12τ τ12t + ω12
t+1 (6.2)
For the transition of τ1t and τ2t , I still use the specification as in (6.1).50 Table A-1, A-2 and A-3 in
the appendix show the results.
6.2 The Second Step: Recovering Structural Parameters
The first step recovers policy functions and the law of motion for states. The second step finds
parameters that rationalize these observed policy functions as the optimal actions.
One benefit of the BBL method is that it significantly reduces the computational burden.
This is because the profit (conditional on adoption) and adoption cost functions are linear in all
parameters, and thus, are the value functions. This method avoids computing the value functions
many times for different sets of parameters. I apply forward simulation to obtain the choice-specific
value functions to estimate the parameters.
For each state sit, I simulate the paths of play for every action that hospital i might take.
In each path, I draw choice-specific shocks for each hospital in each period, combined with the
observed state to determine the choices. States evolve as outlined in Section 6.1. The future path
50I also examine the specification of AR(2), but the coefficients on the second lagged terms are not significant.
30
of play is simulated for a long period (100 periods), until the discounted present value of profits is
sufficiently small. The discount factor β needs to be fixed for econometric purposes, and I fix it
at 0.9 in the paper.51 For each simulated path of play, I obtain the discounted present value of all
the payoffs. I then simulate for S = 1000 times and obtain the choice-specific value function as the
mean of these discounted present values.52 The probability of each action is computed by using
the aggregation properties of the extreme value distribution of private shocks. The estimates are
recovered by maximizing the probabilities of the observed action.
There are two types of active hospitals: potential adopters and Level 1 adopters. I first illustrate
the case for potential adopters in detail.
In every period, potential adopter i chooses from “Not Adopt”(a = 0), “Adopt Level 1”(a = 1),
and “Adopt Level 2”(a = 2). I simulate the path of play for each action that hospital i might take,
as specified in Section 6.1. The unconditional per-period payoff function for hospital i at time t is
π
(sit, σit(s)|θ
)= φ(sit|θ)− C
(sit, σit(s)|θ
)− ε(σit(s)
)(6.3)
For each simulated path s conditional on action ait, I simulate for T = 100 periods, and compute
the discounted present value of all the future payoffs:
V s(sit|ait, θ) =T∑τ=0
βτπit+τ (6.4)
Since all the profit functions and adoption cost functions are linear in the parameters, equation
(6.4) can be written as the inner product of the discounted value of the state vector and the vector
of parameters:
V s(sit|ait, θ) = Ds(sit|ait)θ′ (6.5)
where D is the discounted present value of state vectors.53
The choice-specific value function is the expected discounted present value of all future payoffs
for hospital i:
E
( ∞∑τ=0
βτπit+τ
∣∣∣∣∣ sit, σi, σ−i), (6.6)
51Other studies use 0.9 as the discount factor; see, for example, Ryan (2012).52I also simulate for S = 1500 and S = 2000 times, and the results are almost the same.53Note that D includes the expected discounted present value of the private shock ε as well.
31
and can be approximated by:
V (sit|ait, θ) =1
S
∑s
V s(sit|ait, θ) (6.7)
Three choice-specific value functions are generated through this procedure: V (sit|ait = 0, θ),
V (sit|ait = 1, θ), and V (sit|ait = 2, θ), which, respectively, denote the value functions associated
with Not Adopt (ait = 0), Adopt Level 1 (ait = 1), and Adopt Level 2 (ait = 2). I then recover the
conditional choice probabilities predicted by the model: P̂L=0(ait = 0|sit, θ), P̂L=0(ait = 1|sit, θ) as
well as P̂L=0(ait = 2|sit, θ).
P̂ (ait = k|sit, θ) =exp [V (sit|ait = k, θ)]
exp [V (sit|ait = 0, θ)] + exp [V (sit|ait = 1, θ)] + exp [V (sit|ait = 2, θ)]
(k = 0, 1, 2, andLit = 0)
(6.8)
Similarly, I simulate the choice-specific value functions for each level 1 adopter in each period.
Level 1 adopters make decisions about whether to upgrade to Level 2. In this case, Level 1 adopters
stay at Level 1 when a = 1, and upgrade to Level 2 when a = 2. The conditional choice probabilities
predicted by the model are:
P̂ (ait = k|sit, θ) =exp [V (sit|ait = k, θ)]
exp [V (sit|ait = 1, θ)] + exp [V (sit|ait = 2, θ)](k = 1, 2, andLit = 1) (6.9)
After the probabilities of each decision predicted by the model are generated, I use a pseudo-
likelihood estimator by maximizing the model’s probability P̂ of the actions actually taken by the
hospital in the data. This probability is given by
l =∑t
∑i
ln P̂ (ait = kit|sit, θ) (6.10)
where kit is the observed action by hospital i at time t in the real data.
The standard errors of the parameters are estimated using the technique of bootstrapping.
There are 530 markets in my sample. Therefore, I draw ns random samples of 530 markets with
replacement. (Each time, some markets from the original sample may be drawn more than once,
and others may not be drawn.) For each constructed random sample, I estimate the parameters of
32
the model.54 The estimator of the asymptotic covariance matrix is the sample variance of the ns
sets of estimated parameters. I report standard errors using ns = 400 bootstraps.55
7 Structural Parameters
The estimated structural parameters are presented in Table 7. The results show the presence of
competitive effects in the adoption: the parameter for “number of L1 adopters” is significantly neg-
ative for the L1 profit function, and the parameter for “number of L2 adopters” is also significantly
negative for the L2 profit function. Thus, the payoffs from each level decline substantially with the
number of adopters of this level. Moreover, the L1 profit function is also decreasing in the number
of L2 adopters in the market (−0.033), but this effect is quite small and only marginally significant.
That is, the presence of L2 adopters will deter the L2 adoption a lot more than the L1 adoption.
Meanwhile, the L2 profit function does not respond much to the number of L1 adopters. These
varying degrees of competition show the hospitals’ incentives to differentiate from each other along
the adoption levels.
The effect of market concentration on technology adoption is often of great interest.56 In the
case of EMR adoption, my results show the parameters for HHI are insignificant for both the L1
and L2 profit functions. This suggests that the concentration level of the hospital market does not
play a role in the EMR adoption, once the competition level of EMR adoption is controlled for.
Karaca-Mandic et al. (2017) study the adoption of medical technology of drug-eluting stents, and
find the similar results.
The other results are as expected. Hospitals with more beds benefit more from EMR adoption.
Markets with more admissions have greater demand for healthcare, which results in higher profits
from L2 adoption. The results also show that markets with more persons eligible for Medicare have
greater benefits from L2 adoption, but lower benefits from L1. This indicates that such markets
have a strong need for the advanced EMR applications. The parameters for market-category effects
in the profit functions are all positive and significant. Moreover, they are increasing as the markets
54For each bootstrapped sample, I re-estimate all of the stages of estimation procedure, so the resulting standarderrors reflect the multistage nature of the procedure.
55I have used different numbers of bootstraps, including 200, 300, and 400, and the results are quite similar.56Gowrisankaran and Stavins (2004) find that firms in concentrated markets are more likely to adopt the automated
clearing house electronic payments system. Freedman et al. (2018b)show that hospitals have more incentives to choosethe same EMR vendors (agglomeration) in more competitive markets.
33
Table 7: Structural Parameters
L1 L2
Number of L1 adopters -0.207*** 0.019(0.029) (0.014)
Number of L2 adopters -0.033* -0.268***Profit (0.018) ( 0.044)
Log of number of beds 0.071*** 0.111***(0.014) (0.015)
HHI -0.033 0.013(0.052) (0.059)
Log of total admissions -0.047 0.388***(0.046) (0.076)
Log of number of persons eligible -0.194*** 0.464***for Medicare (0.032) (0.069)Percent of persons in poverty -0.263 0.122
(0.166) (0.220)Market-category effects:
between the 10th and 20th percentiles 0.467*** 0.711***(0.106) (0.103)
between the 20th and 30th percentiles 0.479*** 0.883***(0.108) (0.119)
between the 30th and 40th percentiles 0.606*** 1.119***(0.114) (0.145)
between the 40th and 50th percentiles 0.756*** 1.308***(0.118) (0.158)
between the 50th and 60th percentiles 0.806*** 1.415***(0.122) (0.182)
between the 60th and 70th percentiles 0.972*** 1.496***(0.130) (0.198)
between the 70th and 80th percentiles 1.047*** 1.758***(0.136) (0.219)
between the 80th and 90th percentiles 1.184*** 1.913***(0.148) (0.236)
above the 90th percentiles 1.471*** 2.240***(0.167) (0.264)
L0 to L1 L0 to L2 L1 to L2
Constant 8.017*** 27.214*** 22.120***Cost (1.116) (1.824) (2.114)
Year effects -0.470*** -0.822*** -0.930***(0.119) (0.105) (0.108)
∗∗∗p < .01,∗∗ p < .05,∗ p < .10.
34
move from the lowest percentile range to the highest. This is consistent with the way in which
I define the market-category effects. In the cost functions, we observe negative and significant
parameters for year effects. As year effects follow AR(1) and increasingly converge to the steady
state, the negative parameters indicate that the costs of EMR are decreasingly converging over
time. In reality year effects for EMR adoption could also capture the change in people’s preference
for EMR and pressure from the government, etc. Thus, my estimates of cost here capture not only
the pure cost for this technology per se but also the adoption trend.
To adopt EMR technology with L2 applications such as CPOE, U.S. hospitals need to spend
an average of $80, 000 to $100, 000 per bed, for the required project planning, software, hardware,
implementation, and training (Laflamme et al., 2010). Dranove et al. (2015) point out that the
cost of installing and operating an EMR system by an average-sized hospital is at least $10 million
and could be much higher. The average number of beds for hospitals in my sample is 99, and $10
million would translate to around $100, 000 per bed. The costs provided by these two papers are
roughly consistent. I apply these estimates here, and assume that the costs of adopting L2 EMR
are $100, 000 per bed in 2008. This would translate to upfront costs to implement Level 2 in 2008 of
$9, 900, 000 for an average hospital in my dataset that has 99 beds. From Table 7, the initial costs
for an average potential adopter to adopt Level 2 are 27.214 units in 1999 and 24.647 in 2008.57
By equating 24.647 units to $9, 900, 000, 1 unit would stand for $401, 672. To put these results into
context, an average potential hospital with 99 beds in my dataset would pay costs of $3, 082, 431
(7.674 units) to adopt Level 1 and $9, 900, 000 to adopt Level 2 in 2008. An average L1 adopter
would pay costs of $7, 583, 969 (18.881 units) to upgrade to L2.
Regarding the profits, the average hospital in an average market would receive profits of $273,940
(0.682 units) per year after adopting Level 1, and would receive profits of $813,787 (2.026 units) per
year after adopting Level 2. The competitive effects are large in terms of profits. For an average
hospital, one more L1 adopter in the market would decrease its annual profits from adopting Level
1 by $83,146 and its annual profits from adopting Level 2 by $13,255, keeping other variables
constant. If there were one more L2 adopter in the market, an average hospital’s annual profits
from L2 would decrease by $107,648. I further discuss the competitive effects and measure their
5724.647 is computed as 27.214 + (−0.822) × (3.123), where 3.123 is the year effect of 2008 for L2 adoption fromTable 3.
35
magnitude in the counterfactual experiments in the following section.
8 Experiments
The estimated structural parameters, along with the underlying theoretical model, allow me to
perform the counterfactual experiments. Through solving for the equilibrium outcomes, and sim-
ulating hospitals’ adoption behavior, my first class of experiments analyzes the competitive effects
during the adoption process and the strategic interaction between hospitals. To what extent would
competitive effects affect the adoption times? Do hospitals have preemptive adoption? These are
the primary questions I aim to address.
The second class of experiments evaluates the government’s incentive plans for EMR. First, I
evaluate the effectiveness of the policy. To what extent would the policy spur adoption? Would
the effectiveness vary by hospital or market characteristics? Is the policy cost-effective? Second,
I examine alternative design of the subsidy policy, to assess whether adoption could be further
accelerated. Finally, I study the role that competition plays in the effectiveness of the incentive
plans. Competitive effects for EMR adoption are typically overlooked by researchers and policy-
makers. To what extent would the effectiveness of the subsidy policy be affected by the competitive
effects?
The remainder of this section is structured as follows. Section 8.1 describes the method I use
to solve the equilibrium outcomes. Section 8.2 examines the role that competitive effects play in
the adoption process. Section 8.3 evaluates the subsidy policy.
8.1 Method
Based on the estimated structural primitives and the Pakes and McGuire (1994) algorithm, I solve
the finite-state equilibrium outcomes for hypothetical monopoly markets and symmetric duopoly
markets, in order to perform the counterfactual experiments. Ideally, the MPNE for every market in
the sample could be solved. The computational burdens prevent me from doing this. Nevertheless,
it would be very informative and important to study monopoly and duopoly markets, considering
that my study focuses on concentrated markets.
The state vector for a hospital at adoption level Lit, besides the private shocks εit, is denoted
36
by
sit = {n1jt, n2jt, hi, zjt, τt},
where n1jt and n2jt are the discrete-valued endogenous variables, hi, zjt, τt are the exogenous vari-
ables, and εit is the vector of private shocks. For simplicity, the exogenous hospital and market
variables hi, zjt are assumed fixed. These variables include the number of beds for each hospi-
tal, HHI, total hospital admissions, number of persons eligible for Medicare, percent of persons
in poverty, and market-category effects. Previous results show that it is important to take the
time trend into consideration (e.g., Dranove et al., 2015) .58 It is particularly important for dy-
namic models, since forward-looking agents rely on the trend to make better decisions regarding
the adoption timing. Year effects τ1t , τ2t and τ12t are assumed to follow an AR(1) process in my
estimation, as discussed in Section 6.1.2. I discretize each of them to 10 levels, and compute the
transition matrix, based on the method of Tauchen (1986). This method allows me to choose values
for the year effects and the transition probabilities so that the resulting finite-state Markov chain
mimics closely the underlying continuous-valued autoregression. See the Appendix for more details.
Note that there is a permanent drop in the constant term for the AR(1) process of τ12t from 2006.
Therefore, I compute the MPNE from 2006, and simulate hospitals’ behavior since then.
For a hospital at level L, the variation of its state is characterized by (n1jt, n2jt, τt), as variables
hi, zjt are assumed constant. In my model, there are 3, 000 possible states for the hospital in
a monopoly market, and the number of states would be 6, 000 for each hospital in a symmetric
duopoly market.59 Let sk denote the k-th state, and let V0(s), V1(s), and V2(s) denote the value
functions for potential adopters, Level 1 adopters, and Level 2 adopters, respectively, at state s.
Using the aggregation properties of the extreme value distribution of the private shocks ε, the
58Dranove et al. (2015) point out that, prior to the policy, there was a steadily rising trend for EMR adoption,and thus, at least part of the growth after the policy is simply the continuation of this pre-existing trend.
59For the monopolist, the values of (n1jt, n2jt) could be (0, 0), (0, 1), and (1, 0). For the hospital in a symmetricduopoly market, (n1jt, n2jt) could take six different values, as (0, 0), (1, 0), (0, 1), (2, 0), (1, 1), and (0, 2). Each ofthe year effects is discretized to 10 levels, and thus, τt could take 1, 000 different values.
37
Bellman equations for these value functions can be written as follows:
V0(s) = ln {exp [βMV0(s)]
+ exp [−C(s, L = 0, a = 1) + βMV1(s)]
+ exp [−C(s, L = 0, a = 2) + βMV2(s)]} , (8.1)
V1(s) = ln {exp [φ(s, L = 1) + βMV1(s)]
+ exp [−C(s, L = 1, a = 2) + φ(s, L = 1) + βMV2(s)]} (8.2)
V2(s) = φ(s, L = 2) + βMV2(s), (8.3)
where M is the transition probability matrix, with the kj-element being the probability from the
k-th state sk to the j-th state sj .
Let P0(a|s) denote the probabilities of not adopting (if a = 0), adopting L1 (if a = 1), and
adopting L2 (if a = 2), for a potential adopter (L = 0) in state s. Similarly, let P1(a|s) denote the
probabilities of staying at L1 (if a = 1) and upgrading to L2 (if a = 2), for an L1 adopter in state
s. Based on the value functions of V0(s), V1(s), and V2(s), the probabilities of each action a are:
P0(a|s) =
exp
(−C(s, L = 0, a) + βMVa(s)
)exp(V0(s)
) (a = 0, 1, 2) (8.4)
P1(a|s) =
exp
(−C(s, L = 1, a) + φ(s, L = 1) + βMVa(s)
)exp(V1(s)
) (a = 1, 2). (8.5)
Note that C(s, L = 0, a = 0) = 0 and C(s, L = 1, a = 1) = 0.
If these choice probabilities are known, along with the transition probability matrix for year
effects Mτ , the transition probability matrix M can be computed.60 For example, for a monopolist
at L = 0 in state sk with n1 = 0, n2 = 0 and τ = τk, keeping other variables constant, the
probability of getting to state sj with n1 = 0, n2 = 1 and τ = τ j would be:
M(k, j) = P0(a = 2|sk)Mτ (k, j), (8.6)
60The transition probability matrix for year effects Mτ is discussed in the Appendix, which in my case is a1000-by-1000 matrix, and the kj-th element indicates the probability from the k-th state τk, to the j-th state τ j .
38
where P0(a = 2|sk) is the probability of a potential adopter adopting L2 in state sk and Mτ (k, j)
is the probability from τk to τ j .
I then apply an iterative algorithm to compute the value functions as well as the probabilities
of each choice. The procedure is as follows.
1. Guess a set of initial values for the probabilities of each choice P 0L(a|s) for active hospitals.
2. Use the probabilities of each choice and the transition matrix for year effects Mτ to compute
the state transition matrix M . Then plug M into the Bellman equations (8.1), (8.2) and (8.3) to
compute the value functions for hospitals at different adoption levels.
3. Using the computed value functions from step 2, equation (8.4) and (8.5), calculate a new
set of probabilities of each choice for active hospitals P 1L(a|s).
4 Repeat steps 2 and 3 to generate P 2L(a|s), P 3
L(a|s).,... PnL (a|s), until these probabilities
converge.
After solving the equilibrium values of PL(a|s), I simulate the hospitals’ paths of play in a
monopoly market and a symmetric duopoly market from 2006. My primary interest is the impor-
tance of the competitive effects and the evaluation of the government’s incentive plan.
8.2 Competitive Effects
Industrial Organization researchers have devoted substantial energy to studying relationship of
market structure and the intensity of competition by entry models (Bresnahan and Reiss, 1991;
Berry, 1992; Mazzeo, 2002; Seim, 2006; Augereau et al., 2006). Generally, firms’ entry decisions
rely on entry cost and post-entry revenue, which are functions of the firm’s characteristics, market
characteristics and the intensity of competition. My model of technology adoption is consistent with
the entry model, in which hospitals choose whether and when to enter (or adopt). In this section,
I first quantify the effect of competition on EMR adoption, especially for the adoption of L2 EMR,
as the national implementation of these advanced applications is the goal of the government.61 To
do that, I compare hospitals’ adoption behavior in a symmetric duopoly market, to the scenario
in which they face no competition and act independently. Then I examine whether preemptive
adoption exists. Similar to the method of Igami (2017), I conduct an experiment to remove the
preemption motive in the symmetric duopoly market, by assuming that one hospital A does not
61The use of CPOE is necessary for the Medicare/Medicaid incentive program enacted in 2009.
39
respond to the other hospital B’s adoption behavior. In this case, hospital B does not have the
preemption motive. The preemption is present if hospital B adopts significantly earlier in the
duopoly market with strategic interactions than in the case with no preemptive motive.62
8.2.1 The Effect of Competition on EMR adoption
To quantify to what extent competitive effects affect adoption times, I simulate hospitals’ adoption
behavior in a symmetric duopoly market under two scenarios. The first is based on my estimation
results, in which hospitals compete in the adoption process. I refer to the model in the first case as
the baseline model. In the second scenario, I assume that hospitals make decisions independently,
as if they were in a monopoly market with no other hospitals to compete with in the adoption
process.63 My experiment identifies the competitive effects because that first, the hospitals are
assumed to have the same characteristics and hospital heterogeneity is controlled for.64 Second,
market characteristics are also assumed to be the same under the two scenarios. Therefore, the
competitive effects could be quantified by comparing hospitals’ behavior in the two cases.
Specifically, suppose that the hospitals in my experiment have 100 beds, and are initially poten-
tial adopters. The hypothetical markets are all assumed to have 15, 000 hospital admissions each
year, 30, 000 persons eligible for Medicare, and 20% of people in poverty. Regarding the market
category effects for EMR profitability, the markets are between the 40th and 50th percentiles. The
hospitals’ paths of play starting from 2006 are simulated, based on the equilibrium probabilities
computed from Section 8.1. The simulation number is 10, 000, and I obtain the timing of adoption
by averaging over the 10, 000 simulations.
The simulation results are reported in Table 8.65 The average time needed to adopt L2 of
EMR is substantially shorter for the potential adopters that act independently as if they were in
a monopoly market, and the difference is as large as 11.47 years. To delve deeper into the reasons
for this large discrepancy, I compute the average time when the first of the two hospitals adopts L2
EMR over all the simulations, and also the average time when the second adopts. The difference
62A and B are identical hospitals except for the private shocks in each period.63Note that hospitals in both scenarios are forward-looking. Thus, hospitals that act independently will also take
the adoption trend captured by year effects into account.64Note that the two hospitals in the duopoly market have i.i.d. private shocks, and their draws can be different
in the simulations. Nevertheless, I assume that each hospital’s draws are the same in each period in each simulationunder the two scenarios, to ensure the differences are not caused by the private draws.
65All hospitals adopt Level 2 eventually in my simulations.
40
is small between the times when the first hospital adopts L2 EMR in the case with competition
and in the case without competition (7.40 years vs. 6.79 years). The first adoption is slightly later
in the case with competitive effects, because forward-looking hospitals realize the benefits from
adoption will decrease as the other hospital adopts EMR in the future. We observe a very large
difference in the times when the second hospital adopts L2 EMR in the two cases. The time needed
is 41.51 years in the former case and 19.05 years in the latter. In the baseline model, once the first
adoption occurs, the second hospital’s potential profits from adoption would be greatly reduced,
and its adoption would be significantly deterred. As a result, we find that the large discrepancy
in the first row of Table 8, which shows the average time for L2 adoption (24.28 years vs. 12.81
years), is mainly driven by the delay to the second adoption in a competitive environment.
Table 8: Simulation Results of Hospitals in a Duopoly Market (Starting From L = 0)
With WithoutDifference
Competition Competition
Average time for L2 adoption 24.28 12.8111.47
(0.329)
Average time when the 1st adoption7.40 6.79
0.61of L2 EMR occurs (0.082)
Average time when the 2nd adoption41.51 19.05
22.46of L2 EMR occurs (0.385)
The time span (year) is 200, and the number of simulations is 10000. Standard errorsare in parentheses.
From these experiments, I find that competitive effects in a duopoly market would greatly
deter adoption, particularly for the second adoption. Previous studies typically attribute the low
adoption of EMR to concerns about adoption costs or patients’ privacy, but ignore the competitive
effects. Based on my findings, the competitive effects also play a very important role in hindering
adoption. These results shed light on the subsidy policy designed to promote national adoption of
EMR technology: A policy strategy capturing market heterogeneity in competitive effects would
be more effective for achieving this goal. This policy analysis is further discussed in Section 8.3.3.
41
8.2.2 Preemption
In a dynamic adoption game with competitive effects, a potential adopter may have the preemptive
motive by adopting sooner than in the scenario in which its rivals do not respond to its adoption.
By preemption, the hospital would enjoy the monopolist’s profits for a longer period, because its
adoption would decrease the rivals’ adoption profits as a result of competitive effects, and hence
deter the rivals from adoption. Thus, if the competitive effects are substantial, hospital would
engage in preemption in the adoption process. To examine whether the preemption exists in
the symmetric duopoly market, I conduct a counterfactual experiment to remove the preemptive
motive. I assume that one hospital (named as hospital A) does not respond to the other hospital
B’s adoption behavior, so that B does not have the preemptive incentive. My focus is on how
hospital B differently best responds to such a hypothetical hospital A, compared to the baseline
model that captures hospitals’ strategic interactions.
Specifically, hospital A ignores hospital B’s adoption and makes adoption decisions as if in the
baseline model with modified states. For example, if hospital A is in the state where hospital A is
at L0 and hospital B is at L2 (n1 = 0 and n2 = 1), hospital A will follow the baseline strategy as
if in the state where both hospitals are at L0 (n1 = 0 and n2 = 0).66 Then I solve for hospital B’s
strategy in this case.
Through simulations, I find that it takes 24.43 years on average for hospital B to adopt L2
EMR in this no-preemption experiment. Hospital B adopts 0.15 years earlier in the baseline model
(24.43 years vs. 24.28 years), and this difference is not statistically significant. Therefore, I find no
evidence of preemption in the adoption process. The reason could be that the competitive effects
are not large enough for hospitals to engage in preemption.67
66My method is similar to Igami (2017). He examines to what extent incumbents preempt potential entrants byinnovating more aggressively in the hard disk drive industry. In his no-preemption counterfactual experiment, heforces the potential entrants to ignore incumbents’ innovation behavior, and follow the strategy in the baseline modelthat captures strategic interactions, but with a modified state.
67In another counterfactual experiment, I increase the competitive effect by decreasing the parameter for numberof L2 adopters in the L2 profit function by 30% (from −0.268 to −0.348), and find that hospital B would adoptapproximately 1 year earlier in the baseline model than in the no-preemption experiment. This preemption effect isstatistically significant at the 5% significance level.
42
8.3 Evaluation of Stimulative Plans
I perform policy experiments to evaluate the stimulative plans for EMR adoption. In 2009, the
American Recovery and Reinvestment Act devoted an estimated $27 billion and established a
Medicare/Medicaid incentive program to stimulate adoption of EMR technology, motivated by the
low adoption rate up to that point.68 As reported by the Centers for Medicare & Medicaid Services,
by October 2018, more than $24.8 billion in payments had been made in the Medicare incentive
program and more than $6 billion in the Medicaid incentive program, and more than 642,600
eligible professionals, eligible hospitals, and critical access hospitals had been actively registered in
the Medicare/Medicaid incentive programs.69
Although adoption rates have risen substantially since the announcement of the incentive pro-
gram, the extent to which the recent increase can be attributed to the program is unclear. As
adoption rates were already increasing on their own, critics have argued that hospitals would have
adopted EMR even if the incentives had not been put into place, and the financial incentives sim-
ply substituted public money for private funds (Adler-Milstein and Jha, 2017). Previous studies
evaluating this program are based on statistical results or reduced-form regressions (Adler-Milstein
et al., 2013; Adler-Milstein and Jha, 2017; Dranove et al., 2015; DesRoches et al., 2013), which
would offer limited counterfactual analysis. Based on the underlying structural model, which de-
scribes hospitals’ decision-making and captures the year effects of adoption, my experiments seek
to address this concern and offer a more accurate assessment of this policy.
Previous results in Tables 2, 3 and 7 show heterogeneity in the adoption likelihood across both
hospitals and markets. For example, the likelihood is small for hospitals with fewer beds or markets
with fewer hospital admissions. The results are consistent with previous studies (DesRoches et al.,
2013; Jha et al., 2009; Adler-Milstein et al., 2013). However, studies of how hospitals in different
scenarios would respond to the incentive program are very rare. Would the policy’s effects vary
across hospitals and markets? In which case would it be mostly effective? My experiments answer
these questions by providing quantitative results.
This kind of subsidy policy is often used by the government as a way to encourage entry, which
68This incentive program was later renamed Promoting Interoperability Programs in 2018, with an increased focuson interoperability and improving patient access to health information.
69https://www.cms.gov/Regulations-and-guidance/legislation/EHRIncentivePrograms/DataAndReports.html,accessed June 20, 2019.
43
raises the question of how to design the subsidy policy in the case of EMR adoption to make better
use of public money. This question is especially interesting in a dynamic environment, as the
announcement of such a policy would immediately change a hospital’ belief about its current and
future environment. My experiments explore some alternative design options of this subsidy policy,
in order to examine whether hospitals would have adopted EMR earlier in these cases compared to
the real case. This result may shed light on the optimal future design of such subsidy policies.
Finally, I study the impact of competitive effects in the adoption process on the incentive pro-
gram. As discussed in Section 8.2, competitive effects play a significant role in hospitals’ adoption
behavior. Would they also significantly affect the policy’s effectiveness?
In Section 8.3.1, the EMR incentive program is introduced and explained. In Sections 8.3.2
and 8.3.3, hospitals’ adoption behavior is simulated in monopoly and duopoly markets, in order to
examine the above mentioned questions.
8.3.1 The Incentive Program
The program is essentially a subsidy-based incentive plan that gives payments to eligible hospi-
tals and professionals who demonstrate “meaningful use” of EMR. The meaningful use definition
requires that hospitals adopt and meaningfully use EMR to meet a set of core objectives, such
as using CPOE for medications, recording demographics, maintaining up-to-date problem lists,
and providing patients with an electronic copy of their health information upon request.70 Again,
my experiments focus on the effects of this incentive program on the adoption of L2 applications,
instead of hospitals’ status regarding “meaningful use”. Similar to previous studies that evaluate
this stimulative plan (see, e.g., Dranove et al., 2015), the available data prevent researchers from
measuring whether a hospital has met these standards of meaningful use. More importantly, the
adoption of L2 applications such as CPOE is necessary for a meaningful user, and most hospitals
with such applications plan to apply for the rewards from this incentive program by meeting the
meaningful use requirements (Botta and Cutler, 2014). Therefore, substantial policy insights can
be gained by studying the program’s impact on the adoption of L2 applications.
Under the Medicare/Medicaid incentive programs, eligible hospitals that demonstrate meaning-
70More details about this incentive plan and “meaningful use” can be found athttps://www.cms.gov/Regulations-and-Guidance/Legislation/EHRIncentivePrograms/index.html, accessed June 20,2019.
44
ful use can begin receiving annual payments in any year from 2011 to 2015, for a consecutive 4-year
period.71 Payments consist of a base amount, a discharge related amount and a Medicare/Medicaid-
share related amount.72 Furthermore, the annual payments decrease over this 4-year period, mea-
sured by a “transition factor” (i.e., the initial amount in the first year diminishes by 25% for each
following year). Hospitals receive a total of approximately 250% of the first-year payment. For
instance, the average potential adopter as of 2008 could have expected to receive $2.1 million for
the first year and $5.3 million in total (Dranove et al., 2015). As the adoption costs of the advanced
EMR applications are at least $10 million, these incentives represent approximately 50% (or less)
of the adoption costs for a typical hospital.
In the experiment, I assume hospitals would receive the one-shot payments totaling 50% of the
adoption costs of L2 applications in any year from 2011 to 2015, if they had adopted L2 EMR
by then.73 For example, if a hospital were to adopt L2 before 2011, say, in 2009, it would receive
50% of the adoption costs in 2011; if it were to adopt in 2012, it would receive these payments
in 2013. For hospitals facing higher adoption costs, or receiving lower incentives, the subsidies
might represent a smaller percentage of adoption costs. Thus, my experiments also examine the
cases when the percentages are 30% and 10%. Because of data limitations, I cannot capture the
heterogeneity of hospitals’ rewards precisely in my experiments. By studying the cases in which
large/small hospitals receive different amounts of payments (50%, 30%, and 10% of adoption costs),
the paper attempts to capture some extent of the heterogeneity.74
8.3.2 Monopoly Markets
My first class of experiments focuses on monopoly markets, in which there is lack of the competitive
effects for EMR adoption. The effects of subsidy policy on duopoly markets with competitive effects
are studied in the next section. Specifically, my experiments simulate the hospital’s adoption
71The Medicaid program provides payments based on a “theoretical” 4 years. The overall amount is calculatedonce, and paid over a minimum of 3 years and a maximum of 6 years.
72The amount decreases for hospitals that start getting paid in 2014 and 2015 under the Medicare program. Forexample, if a hospital could demonstrate meaningful use by 2011, it could receive annual payments from 2011 to2014; if a hospital were to begin to receive payments from 2015, it would receive payments for 2015 and 2016.
73The adoption costs of L2 are based on the estimated values in 2008 in my model.74Hospitals that are not meaningful users are subject to a Medicare downward payment adjustment beginning in
2015, unless they can show that compliance with the requirement for being a meaningful EHR user would result insignificant hardship. This penalty-based scheme is not captured in my experiments, as I aim to focus on the subsidy-based program. Moreover, the penalty is only for the Medicare program, and the amount is difficult to measure basedon the available data and studies.
45
behavior for four scenarios in a monopoly market: 1. a medium hospital with 100 beds in a market
with 15,000 hospital admissions; 2. a smaller hospital with 50 beds in a market with 15,000 hospital
admissions; 3. a larger hospital with 200 beds in a market with 15,000 hospital admissions; and 4.
a medium hospital with 100 beds in a larger market with 20,000 hospital admissions.75
First, I simulate the times taken to adopt L2 EMR with no subsidies as the status quo. The
results are shown in Column I in Table 9. In Case 1 without the policy, it would take approximately
12 years for a medium-sized hospital with 100 beds in a market with 15,000 admissions to adopt
L2 from 2006 (i.e., the hospital would adopt L2 EMR in 2017). Relative to Case 1, a smaller
hospital with 50 beds in Case 2 would adopt 2 years later. A larger hospital with 200 beds in
Case 3 would adopt one and half years earlier compared to Case 1, and the hospital with 100 beds
in a larger market with 20,000 admissions would adopt the earliest (Case 4). We clearly observe
the heterogeneity in hospitals’ adoption behavior: large hospitals adopt earlier, and hospitals in a
large market also adopt earlier. In particular, a hospital in a large market with 20,000 admissions
in Case 4 would have adopted by 2015 in the absence of the policy. Therefore, the current policy
might not be very cost-effective, by not taking market heterogeneity into consideration.
With this incentive policy announced in 2009, hospitals will receive the subsidies in any year
from 2011 to 2015, if they adopt L2 EMR by then. Hospitals’ behavior under this circumstance is
simulated and reported in Column II. Three cases are examined, in which the payments are 50%,
30% and 10% of the adoption costs. Note that the numbers in parentheses are the differences from
the status quo without the policy. The numbers represent the years by which the policy shortened
the time to adoption and thus, are indicators for the policy’s effectiveness. From the results, we
observe the following patterns. First, the policy is generally effective, as hospitals would have
adopted much earlier, and would have adopted L2 EMR by 2015 in all cases. Second, the policy
is more effective for the cases in which hospitals would need more time to adopt in the absence
of the policy. For example, it takes the longest time for the hospital in Case 2 (50 beds, 15,000
admissions) to adopt with no subsidy, and the policy is mostly effective for this case (years needed
are shortened by 8.71, 8.37, and 5.40 if the percentages are 50%, 30% and 10%, respectively). The
policy has smaller effects on hospitals that have large adoption likelihood in any case. Thus, the
75Other market characteristics are kept constant. The market is assumed to have 30,000 persons eligible forMedicare and 50% of people in poverty and is between the 40th and 50th percentiles for market-category effects. Asdiscussed in Section 8.1, the simulations start from 2006.
46
Table 9: Simulation Results: Years Needed to Adopt L2 (from 2006) in Monopoly Markets
Without Policy With Policy
SubsidyAmount
The Real Announce Announce Only forDesign in 2008 in 2007 2011
I II III IV V
1 100 beds, 11.95
50% 5.10 4.77 4.48 4.79
(Effect) (6.85) (7.18) (7.47) (7.16)
30% 5.38 4.99 4.67 4.93
15K admissions (Effect) (6.57) (6.96) (7.28) (7.02)
10% 7.55 7.22 6.95 8.54
(Effect) (4.40) (4.73) (5.00) (3.41)
2 50 beds, 13.99
50% 5.28 4.93 4.62 4.93
(Effect) (8.71) (9.06) (9.37) (9.06)
30% 5.62 5.34 5.09 5.17
15K admissions (Effect) (8.37) (8.65) (8.90) (8.82)
10% 8.59 8.20 7.91 10.04
(Effect) (5.40) (5.79) (6.08) (3.95)
3 200 beds, 10.41
50% 4.91 4.67 4.43 4.65
(Effect) (5.50) (5.74) (5.98) (5.76)
30% 5.15 4.91 4.69 4.75
15K admissions (Effect) (5.26) (5.50) (5.72) (5.66)
10% 6.82 6.51 6.27 7.45
(Effect) (3.59) (3.90) (4.14) (2.96)
4 100 beds, 9.27
50% 4.85 4.62 4.40 4.60
(Effect) (4.42) (4.65) (4.87) (4.67)
30% 5.07 4.85 4.63 4.67
20K admissions (Effect) (4.20) (4.42) (4.64) (4.60)
10% 6.34 6.09 5.88 6.73
(Effect) (2.93) (3.18) (3.39) (2.54)
The number of years needed to adopt L2 EMR is calculated as the mean values of 10,000simulations. The time span is 200 years in each simulation. All hospitals start from L = 0.The differences from the status quo in Column I are shown in parentheses.
47
effectiveness varies by the situation. For example, large hospitals would be affected less than small
hospitals given the same level of subsidy, and would be more likely to have adopted before 2015
even with no subsidy. More attention should be paid to smaller hospitals to ensure nationwide
adoption. Furthermore, the current policy completely ignores market heterogeneity. By comparing
Case 1 with Case 4, we observe that a smaller market could be greatly motivated to adopt with the
subsidies but would still lag behind a larger market. Therefore, an effective policy strategy needs
to take market heterogeneity into consideration.
Before the announcement of this incentive program in 2009, such methods to speed up the
adoption of EMR technology went through years of bipartisan support and broad consensus. It
would be interesting to examine whether the policy would be more effective had this incentive
program been passed earlier. This is particularly interesting in a dynamic environment, in which
hospitals are forward-looking. Right after the announcement of the policy, hospitals would have
adjusted their adoption behavior accordingly, as their option value of adopting would have increased
by getting the subsidies sometime in the future. Thus, I simulate hospitals’ adoption times if the
incentive program had been announced in 2008 or 2007. The results are reported in Columns III
and IV, respectively. We observe clearly that the policy would be more effective in all cases, as
the years needed to adopt are shortened compared to the real case of the policy being announced
in 2009.76 In particular, if the policy had been announced in 2007, hospitals would generally have
adopted half a year earlier. This result shows that by simply speeding up the policy-making process
or announcing the policy earlier, adoption would have been accelerated.
Another alternative design of this subsidy policy is subsidizing adoption in only early periods.
For example, Fan and Xiao (2015) find that, in the U.S. local telephone industry, subsidies in only
early periods would reduce the option value of waiting and accelerate entry. If adopters could
receive a considerable and one-shot payment only in 2011, hospitals would have further sped up
their adoption with the hope of obtaining the subsidy in 2011. Thus, it is possible that hospitals
would have adopted earlier than in the case with the real policy design. However, this modified
policy may fail, in that the amount of subsidies is not enough for hospitals to have covered the costs
and adopted earlier before 2011; then, the adoption probabilities would have returned to low levels
as there would have been no subsidy after 2011. In this circumstance, we may observe hospitals
76All the differences are statistically significant at 5% significance level.
48
adopting later than in the case with the real policy design. Hence, I simulate hospitals’ adoption
times under this alternative policy design, and the results in Column V confirm the expectation.
Relative to the case with the real policy design (Column II), if the subsidy had been 50% or 30% of
adoption costs, the adoption process would have accelerated further. However, if the subsidy had
been only 10% of the adoption costs, hospitals would have adopted later.
In summary, my experiments show that the incentive program is generally effective for encour-
aging adoption, and is more effective in cases in which hospitals have otherwise small adoption
probabilities. To make the policies more effective, hospital and market heterogeneities need to be
taken into consideration. For example, large hospitals would be affected less than small hospitals
given the same level of subsidy, and would be more likely to have adopted before 2015 even with no
subsidy. Thus, more attention needs to be paid to small hospitals to ensure nationwide adoption
and to make the incentive program more cost-effective. Additionally, the current policy completely
overlooks market heterogeneity. Hospitals in a large market tend to have adopted EMR before 2015
even with no subsidy, while hospitals in a small market are less likely to have adopted EMR with
no subsidy, and would still lag behind even with the subsidy.
Several alternative design options of this incentive program are examined. If the policy had
been announced earlier than 2009, hospitals would have further accelerated adoption. Particularly,
hospitals would generally adopt half a year earlier had the policy been passed in 2007. Moreover,
if the policy had subsidized adoption only in 2011, its effectiveness would depend on the amount
of subsidies. Compared to behavior in the case with the real policy design, hospitals would have
adopted earlier if the amount of subsidies were considerably large, but would have delayed adoption
if the amount were small.
8.3.3 Duopoly Markets
As shown in Table 8, competitive effects in a duopoly market would substantially deter EMR
adoption, particularly for the second adoption. This opens up the question of whether competitive
effects affect the effectiveness of the subsidy policy. In other words, given the same incentive plan,
how would hospitals behave differently with and without the competitive effects?
Theoretically, the subsidy lowers every potential adopter’s adoption costs. If there is a strong
competitive effect, a potential adopter has to balance the lower adoption costs and the lower adop-
49
tion benefits due to enhanced competition, which is a (partial) equilibrium effect. To examine this
effect, hospitals’ adoption times are simulated in duopoly markets. Similar to Section 8.2, two sce-
narios are considered. The first is based on the estimation results, and captures competitive effects
in the adoption process. The second scenario assumes that hospitals make decisions independently,
as if they were in a monopoly market with no others to compete with in the adoption process. The
configuration is the same as in Section 8.2: hospitals have 100 beds, markets have 15, 000 hospital
admissions, 30, 000 persons eligible for Medicare, 20% of people in poverty and are between the
40th and 50th percentiles.77
Again, to evaluate the effectiveness of the subsidy policy on duopoly markets, I examine three
cases in which the subsidies equal 50%, 30%, and 10% of the adoption costs, respectively. Moreover,
as in the real design in Section 8.3.2, hospitals receive the subsidies in any year from 2011 to 2015 if
they adopt L2 by then. The results are reported in Table 10. In the scenario with no competition
during the adoption process, the policy is very effective: it takes at most 11.09 years for hospitals
to adopt L2 in all cases (i.e., hospitals would have adopted L2 by 2016). However, in the scenario
with competitive effects, although the policy would substantially spur adoption, hospitals still adopt
later than in the scenario without competition. This difference in adoption times is more significant
if the subsidy is lower. Specifically, if the subsidies are 10% of the adoption costs, the first adopter
would adopt by 2011 (5.55 years in Column II) in a competitive environment, while the second
adopter would adopt approximately 2033 (28.19 years in Column II).
These findings suggest that by ignoring competitive effects during the adoption process, one may
over-predict the effectiveness of the subsidy policy. The policy would be very effective if there were
no competitive effects in the adoption process, in the sense that hospitals in all cases would have
adopted by 2016. If the competitive effects are taken into account, the policy would still greatly
spur adoption, but hospitals lag behind relative to the case without competition (Column II vs.
Column IV), especially for the second adopter, because the first adopter decreases the potential
benefits of adoption for the later adopter. As a result, a policy strategy accounting for competitive
effects is essential to spur adoption.
77This market configuration is the same as the monopoly market in Section 8.3.2, except that the duopoly markethas an HHI of 0.5, while the monopoly market has an HHI of 1.
50
Table 10: Simulation Results: Years Needed to Adopt L2 (from 2006) in Duopoly Markets
With Competition Without Competition
Without Policy With Policy Without Policy With PolicyI II III IV
Average time for L2adoption
50% 5.41 50% 5.1324.28 30% 6.24 12.81 30% 5.43
10% 16.66 10% 7.97
Average time whenthe first adoptionoccurs
50% 4.47 50% 4.257.4 30% 4.63 6.79 30% 4.35
10% 5.55 10% 4.94
Average time whenthe second adoptionoccurs
50% 6.4 50% 6.0441.51 30% 7.91 19.05 30% 6.55
10% 28.19 10% 11.09
The number of years needed to adopt L2 EMR is calculated as the mean values of10,000 simulations. The time span is 200 years in each simulation. All hospitals startfrom L = 0.
9 Conclusion
This paper studies the multilevel adoption of EMR technologies by U.S. hospitals in concentrated
markets. A dynamic oligopoly model is developed and estimated to capture strategic interactions
among hospitals. I find evidence of competitive effects: the benefits from adopting L1 EMR (L2
EMR) decline as more hospitals adopt L1 (L2) in the market. This result is consistent with vertical
product differentiation along the EMR levels in the adoption process. Previous researchers and
policy-makers have typically overlooked the importance of competitive effects on EMR adoption.
My study shows that hospitals’ adoption of advanced EMR technologies such as CPOE, is greatly
deterred by competitive effects.
The 2009 Medicare/Medicaid incentive programs enacted to promote national adoption of EMR
are evaluated by the counterfactual experiments. First, I find that hospital and market hetero-
geneities need to be taken into account to make the policy more effective. For example, large
hospitals would be affected less than small hospitals given the same level of subsidy, and would
be more likely to have adopted before 2015 even with no subsidy. Similarly, hospitals in a large
market with more hospital admissions are also more likely to have adopted EMR by 2015. In these
cases, government subsidies mostly crowd out private investments. To make better use of the public
51
funds, more attention needs to be paid to small hospitals, and hospitals in small markets, which
would lag behind even with the subsidy. Second, several alternative forms of the subsidy policy are
explored, to shed light on future policy design. Because hospitals are forward-looking, their beliefs
would vary with the change of policy design, and they would adjust their behavior accordingly. I
find that if the policy had been announced earlier, hospitals’ adoption could be further accelerated.
Particularly, hospitals would have adopted half a year earlier had the policy been passed in 2007.
Finally, competitive effects also play an important role in the effectiveness of this policy. Ignoring
competitive effects during the adoption process leads to overestimates of the effectiveness of the
policy.
52
Appendix A: Supplemental Results
Table A-1: Transition of Year Effects for L1 Adoption(τ1t )
Variable Coefficient Standard Error
Constant 0.471 0.263Lag of τ1t 0.637 0.210
Adjusted R-squared 0.506
Table A-2: Transition of Year Effects for L2 Adoption(τ2t )
Variable Coefficient Standard Error
Constant 1.258 0.401Lag of τ2t 0.676 0.125
Adjusted R-squared 0.778
Table A-3: Transition of Year Effects for L2 Upgrade (from L1)(τ12t )
Variable Coefficient Standard Error
Constant 0.802 0.161Dummy if in or after 2006 -0.779 0.225Lag of τ12t 0.940 0.071
Adjusted R-squared 0.976
53
Appendix B: Finite State Markov-chain Approximations for Year
Effects
I present the details of finite state Markov-chain approximations for year effects τ1t , τ2t and τ12t ,
which are assumed to follow an AR(1) process in my estimation. The method is based on Tauchen
(1986).
I illustrate the method by the example of τ1t , which follows the AR(1) process as follows.
τ1t+1 = µ10 + µ11τ1t + ω1
t+1 (B-1)
Let τ̃1t denote the discrete-valued process that mimics this AR(1) process, and τ̄11 < τ̄12 < · · · < τ̄110
denote the 10 values that τ̃1t may take on. Specifically in my counterfactual experiments, I set τ̄11 ,
τ̄12 , . . . , τ̄110 equal to 0, 0.4, . . . , 3.6, and d = τ̄1k − τ̄1k−1 = 0.4.
I then calculate the transition matrix Mτ1 , where Mτ1(j, k) = Pr(τ̃1t = τ̄1k |τ̃1t−1 = τ̄1j ). For each
j, if 2 ≤ k ≤ 9, set
Mτ1(j, k) = Pr(τ̄1k − d/2 ≤ µ10 + µ11τ̄
1j + ω1
t ≤ τ̄1k + d/2)
= F
(τ̄1k + d/2− µ10 − µ11τ̄1j
σω
)− F
(τ̄1k − d/2− µ10 − µ11τ̄1j
σω
),
otherwise, for k = 1 and 10,
Mτ1(j, 1) = F
(τ̄11 + d/2− µ10 − µ11τ̄1j
σω
), Mτ1(j, 10) = 1− F
(τ̄110 − d/2− µ10 − µ11τ̄1j
σω
),
where F (∗) is the cumulative distribution function of the standard normal distribution.
The transition matrix Mτ2 for year effects τ2, and the transition matrix Mτ12 for year effects
τ12 can be calculated in the same way. The transition matrix Mτ for all the year effects, which is
a 1000-by-1000 matrix, can be obtained as the Kronecker product of Mτ1 , Mτ2 , and Mτ12 :
Mτ = Mτ1 ⊗Mτ2 ⊗Mτ12 .
The kj-th element of Mτ indicates the probability from the k-th state τk, to the j-th state τ j .
54
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