the economic burden of carpal tunnel syndrome: long-term earnings of cts claimants in washington...
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AMERICAN JOURNAL OF INDUSTRIAL MEDICINE 50:155–172 (2007)
The Economic Burden of Carpal Tunnel Syndrome:Long-Term Earnings of CTS Claimants in
Washington State
Michael Foley, MA,� Barbara Silverstein, PhD, MPH, and Nayak Polissar, PhD
Background The long-term earnings losses borne by injured workers, beyond thosecovered by workers’ compensation insurance, are rarely estimated. The post-claimearnings of a cohort of carpal tunnel syndrome (CTS) claimants are tracked over a periodof 6 years and compared to the earnings of claimants with either upper extremity fracturesor dermatitis.Methods Quarterly earnings records of 4,443 workers in Washington State who filedclaims with the State Fund in 1993 or 1994 for CTS are compared to those of 2,544 withupper-extremity fracture claims and 1,773 with medical-only dermatitis claims.Multivariate regression was used to identify the effect of injury type on earnings fromthat of other potential predictors.Results CTS claimants recover to about half of their pre-injury earnings level relative tothat of comparison groups after 6 years; they also endured periods on time-loss three timeslonger than claimants with upper extremity fractures. CTS surgery claimants had betteroutcomes than those who did not have surgery. Earnings recovery fractions among CTSclaimants were better for workers who: (1) were younger; (2) had stable pre-claimemployment; (3) lived in the Puget sound area; (4) worked for large businesses; (5) workedin non-construction/transportation industries; or (6) were in the higher pre-injuryearnings categories. Cumulative excess loss of earnings of the 4,443 CTS claimants was$197 million to $382 million over 6 years, a loss of $45,000–$89,000 per claimant. Thisunderscores the importance of prevention, early diagnosis, and accommodation for returnto work. Am. J. Ind. Med. 50:155–172, 2007. � 2007 Wiley-Liss, Inc.
KEY WORDS: carpal tunnel syndrome; occupational injuries; occupational diseases;economic impacts; workers’ compensation; cost of illness; disability; employment
INTRODUCTION
The full economic loss that results from work-related
injury goes far beyond the direct covered medical costs,
vocational rehabilitation expenditures, pensions, and wage-
replacement costs that comprise the reported cost of a
workers’ compensation claim. Employers bear a portion of
the full economic loss in the form of indirect cost including
production interruption, accident investigation, and the
recruiting, and training of replacement workers. On the
injured workers’ side there are economic losses borne by
the workers’ families: the loss of the ability to perform
family and social roles, depression, living/working with pain,
impacts to disability and welfare systems, and loss of the
worker’s contribution to community life [Keogh et al., 2000].
Perhaps most significantly, there is the long-term loss of
earnings, which extends beyond the period of wage
� 2007Wiley-Liss, Inc.
Safety and Health Assessment and Research for Prevention (SHARP) Program,Washing-ton State Department of Labor and Industries, Olympia,Washington
*Correspondence to: Michael Foley, Safety and Health Assessment and Research forPrevention (SHARP) Program, Washington State Department of Labor and Industries,P.O. Box 44330, Olympia,WA 98504-4330. E-mail: [email protected]
Accepted 7 December 2006DOI10.1002/ajim.20430. Published online inWiley InterScience
(www.interscience.wiley.com)
replacement, and is due to the worker’s injury-related loss of
function or skills. Several recent studies, applying a human
capital approach, use data on earnings from state employment
security departments for injured workers and matched control
groups [Biddle, 1998; Boden and Galizzi, 1999; Reville,
1999; Reville et al., 2002]. One technique for estimating long-
term earnings loss is to use multiple regression analysis to
compare the earnings of workers with accepted time-loss
claims to those of workers with medical-only claims.
Covariates such as age, gender, industry, and occupation are
included in these models in order to isolate the separate impact
of injury type on earnings [Biddle, 1998; Boden and Galizzi,
1999]. Another approach is to choose a set of uninjured
workers from state unemployment insurance databases,
matched to each injured worker by initial earnings and firm
or industry [Reville, 1999; Reville et al., 2002]. These studies
show that workers who have time-loss injuries are likely to
experience substantial income losses that continue long after
their wage-replacement benefits end [Reville et al., 2001].
Using a sample of workers with permanent disability claims,
Reville estimated 5-year earnings losses averaged $23,692;
for workers with the most seriously disabling injuries losses
over $90,000 over the same period of time [Reville, 1999].
These earnings losses, together with the unpaid fringe benefits
that workers would have received, provide a lower-bound
estimate of the economic loss to society from the worker’s
reduced output. Although this provides an estimate of the lost
output, it cannot capture the qualitative portion of the burden
of injury.1 It should be noted here that the burden of work-
related injury is measured from the perspective of society as a
whole, rather than from either the worker or the employer’s
point of view. Since wage replacement payments made by the
State Fund to workers with time-loss claims are transfers from
one part of society to another, they are not counted in the
estimates presented here. It is assumed that the economy is at
or near full-employment, so that the loss to society of one
worker’s output due to injury is not offset by the gain to society
from replacing that output by employing a formerly idle
worker. Using a combination of the human capital method
described above and the results of several national surveys,
Leigh has estimated an overall economic loss of about
$155 billion (in 1992 dollars) for all work-related injury and
illness [Leigh et al., 2000]. About half of this cost was
attributed to lost earnings. Using somewhat different methods,
Miller arrived at a similar estimate [Miller, 1997]. The long-
term earnings losses experienced by injured workers may be
due to incomplete recovery of physical function prior to return
to work, or they may be due to labor market effects of the
worker’s injury-related absence which may persist long after
the worker recovers. These effects include loss of pre-injury
job, loss of seniority or of investment in job-specific skills.
They may also be due to stigma attaching to the worker with
long periods of injury-related absence. Such workers may
come to be viewed as being ‘‘injury prone’’ or ‘‘unreliable’’
causing the worker to have more difficulty finding employ-
ment or advancement. There is also evidence that the longer
the duration of time-loss the more frequent the episodes of
unemployment after the initial return to work [Galizzi and
Boden, 1996; Eakin et al., 2003].
MATERIALS AND METHODS
In this study the human capital approach is used to
estimate the burden of work-related carpal tunnel syndrome
(CTS). The approach is similar to that used by Reville in that
the earnings of CTS claimants are compared to those of
claimants with other injury types. Ideally, these earnings
should be compared to those of uninjured workers matched
by gender, age, and occupation/industry to the set of injured
workers. Unfortunately it is not possible to obtain data
on gender or age for uninjured workers from the Washington
State Employment Security database. This information is
available, however, for all workers who file a workers’
compensation claim, which allows a comparison of the
earnings profiles of workers with a CTS-related claim to
those of workers with other kinds of injury claims while
controlling for a large number of earnings-related factors
independent of injury type. Two categories of injury were
chosen as comparison groups: workers with an upper-
extremity fracture that resulted in four or more lost work-
days; and workers who filed medical-only claims for
dermatitis. It is assumed that the medical-only dermatitis
claimants would be the claimant cohort most similar to
uninjured workers in terms of their long-term earnings.
While this approach does not permit a calculation of the full
earnings loss a worker bears when they suffer work-related
CTS, any fraction of earnings lost in excess of that suffered
by the workers in the two comparison groups gives a lower
bound estimate of the loss caused by the injury [Biddle, 1998;
Boden and Galizzi, 1999]. Estimates of work-related CTS
incidence based upon frequency of claims are likely to be just
a fraction of the true number of cases, as survey-based
evidence has documented [Biddle et al., 1998; Morse et al.,
2001]; and the total burden of these cases extends well
beyond the direct costs associated with the claims themselves
[Keogh et al., 2000].
Workers’ Compensation Data
Washington State employers, except the federal govern-
ment, and employers of railroad and long-shore workers, are
1 This might be achieved by using other techniques such as ‘‘contingentvaluation,’’ where individuals are asked what they would be willing to payto reduce their risk of an injury or illness by a given amount (Smith andDesvouges, 1987). Another approach quantifies the ‘‘risk premium’’ paidto workers exposed to job hazards (Viscusi, 1993). These approaches havebeen widely applied to fatal risks to derive ‘‘value of life’’ measures, butbecause of their subjectivity, computational complexity, and because theyestimate the value of changes in risk at the margin instead of the totalsocial cost of illness, we define burden as the quantifiable loss to societyof the output of injured workers as measured by lost earnings.
156 Foley et al.
required to obtain workers’ compensation insurance through
the Washington State Department of Labor and Industries
(L&I) industrial insurance system unless they are able to self-
insure. The L&I State Fund provides workers’ compensation
to approximately 160,000 employers and approximately
66% of the covered workforce. The remaining 400 (primarily
large) employers self-insure and employ approximately one-
third of the Washington workforce.2
All Washington workers’ compensation State Fund
claims receive codes for nature, type, body part, source,
and associated source of injury or illness based upon the
American National Standards Institute (ANSI) Z16.2 coding
system [ANSI, 1986].3 These codes are assigned early in the
claims administration process, and represent an initial
definition of the primary injury or illness. ANSI codes can
be used individually or in combination with each other to
identify specific injury or illness claims. ANSI codes can be
combined with ICD-9 diagnosis and CPT procedure codes to
develop case criteria as well.
L&I maintains claims databases for both State Fund and
self-insured employers, however the information collected
from self-insured employers is more limited, has incomplete
claim costs and lost workdays data and does not allow
identification of medical-only cases by ANSI or ICD-9
codes. This led us to restrict this study only to State Fund
claims. The exclusion of self-insured employers means that
claimants employed by the very largest employers in
Washington State were not included in the analysis.
The approach to defining cases of carpal tunnel
syndrome for purposes of this study was to start with a
definition that was narrowly focused upon a limited set of
ANSI codes, which restricted cases to those with an onset
related to overexertion. This first group was then augmented
by drawing in those claims with a more expanded set of ANSI
codes related to the upper extremities. Finally, claims were
added which had diagnosis (ICD-9) or procedure (CPT)
codes consistent with CTS, but not the relevant ANSI codes.
These definitions are displayed in Table I.
The definition of Group 1 has the advantage of being
related specifically to claims related to the wrist or hand area,
and only covering injuries that are classified early in the case
history as being carpal tunnel syndrome. Earnings outcomes
for this group may be affected by this early case diagnosis, so
these are analyzed separately. The disadvantage of restricting
ourselves to this narrow definition of CTS is that it misses
many cases which later turn out to be CTS, but which are not
classified as such because claims are assigned ANSI codes
relatively early in the case history. In addition, with ANSI
TABLE
I.SelectionC
odesforCTS
Cohort,byCTSGroup
Group1
Group2
Group3
Numberofcases
2,123
1,043
1,277
ANSInature
562:Bell’sPalsy
andotherdiseasesofthenervesandperipheralganglia[CTS]
[562],190,260,310,400,560,561,580,995,999:dislocation,inflammationof
joints,tendonsorm
uscles;strains,sprains;multipleinjuries;conditionsofner-
vous
system
;sym
ptom
sofill-defined
conditions;otherinjurynec;unclassi-
fied,notdetermined
Any
AND
AND
AND
ANSIbodypart
320^
350:wrist,hand,fingers
[320^350],300,310,311,313,315,318,398,450:upperextremities;arm(s)
abovew
rist;upperarm;elbow;forearm;arm-multiple;shoulder(s)
Any
AND
AND
AND
ANSIType
120^
124,129:over-exertioninlifting,pushing,pulling,wielding,throwing,
carrying,NEC
[120^124,129],082,083,085,086,100:rubbed
orabradedby
objectsbeing
handled,vibratingobjects,repetitionofpressure;bodilyreaction
Any
AND
AND
ICD-9code
354.0:carpaltunnelsyndrome
354.0:carpaltunnelsyndrome
354.0:carpaltunnelsyndrome
OROR
CPTcode
Any
64721,29848:carpaltunnelreleasesurgery;arthroscopicsurgeryon
thew
rist
64721,29848:
carpal
tunnelrelease
surgery;arthroscopicsurgeryon
thew
rist
2 The L&I State Fund offers elective workers’ compensation coverage forself-employed workers and household employers with two workers orless, and other defined exemptions listed in Revised Code of WashingtonTitle 51. This segment of the workforce accounts for approximately 7% ofthe total employed.
3 A complete description of the L&I claims management database can befound in Silverstein et al. [2002].
Long-Run Economic Burden of CTS 157
coding, only one body area is listed, usually the one identified
as the major area of concern. This is an important limitation
in comparison with the ICD-9 and CPT codes, which come
from medical bills submitted over the course of the claim’s
history, and which can refer to multiple body areas.
Previous research in musculoskeletal disorders con-
ducted with the Washington State workers’ compensation
claims data has shown that the set of ANSI and ICD-9 and
CPT codes in the third column of Table I bring in additional
CTS cases, and this augmented set of cases is called Group
2 [Silverstein et al., 2002]. The selection codes for Group
2 can overlap partially with those for Group 1. For example, a
case with a nature code 562 (Bell’s Palsy and other Diseases
of the Nerves, etc) and a type code of 120 (overexertion), but
a body part code of 398 (arm-multiple areas) would be a
Group 2 case, as long as the diagnosis code is ‘‘354.0’’ (CTS)
or there is a medical procedure code of ‘‘64721’’ (carpal
tunnel release surgery) or ‘‘29848’’ (arthroscopic procedure
on the wrist). The disadvantage of this augmented definition
is that sometimes these cases involve injuries to multiple
body parts, which means that the fraction of the impact on
the worker’s earnings that is related to their carpal tunnel
condition is unknown.
Finally, there are also CTS cases that do not receive a
combination of ANSI codes that would allow one to include
them in either of the above groups. They may have CTS-
related codes for body part or type or nature, but not all three.
However, at some point in their case history these workers do
receive either a medical diagnosis of CTS (ICD-9 354.0) or
a medical procedure related to CTS is performed (CPT
64721 or 29848). This is more likely to occur in workers with
multiple injuries where the main initial injury is something
other than CTS. The selection codes for Group 3 can overlap
partially with those for Groups 1 and 2. For example, a case
with a nature code of 160 (contusion) and a body part code of
331 (upper arm) and a type code of 030 (fall from elevation)
would not be either a Group 1 or a Group 2 case. But if there
was an ICD-9 code of 354.0 on the claimant’s medical bills,
then this is a Group 3 CTS case. These three CTS subgroups
form a comprehensive set of all State Fund compensable
CTS cases filed in the years 1993 and 1994, a total of
4,443 claims.4
Compensable upper-extremity fractures and medical-
only dermatitis claims were chosen as comparison groups.
Fracture cases were used in order to have a comparison group
which, like CTS, involved a significant interference with
ability to work and which often results in a significant period
of lost workdays. This is also a group where, unlike CTS,
the injury is traumatic, with visible signs and unmistakable
work-relatedness, and where the diagnosis and treatment
would follow rapidly after injury onset. Medical-only
dermatitis claims were chosen because a comparison group
was needed with a condition which would not be expected to
result in interference with the worker’s ability to work or
result in long-term productivity loss. This group is a close
approximation to an uninjured control group for whom a full
set of demographic and industry characteristics that predict
earnings could still be obtained.5
For dermatitis the ANSI coding criterion was only that
the claim must have one of the nature codes associated with
dermatitis (Z16.2 nature codes 180–184, 189). This resulted
in 1,773 eligible dermatitis cases being selected. For upper
extremity fractures the coding criteria was any claim with an
ANSI Nature code of 210 (fracture) and with one of the ANSI
Body Part codes associated with the upper extremities:
(Z16.2 Body Part codes 300, 310, 311, 313, 315, 318, 320,
330, 340, 350, 398 or 450). Using these criteria resulted in
2,544 fractures cases.
Data for workers’ compensation claims for carpal tunnel
syndrome, upper extremity fractures, and dermatitis filed
during the calendar years 1993 and 1994 were extracted in
January 1999 from the L&I Industrial Insurance claims
database. Data elements captured included: social security
number; date of injury; birth date; age; claim status
(‘‘compensable’’ lost time claim of 4 or more days or
medical treatment claim only); gender; total cost of claim;
days of time-loss paid; dollar amount of time-loss payments;
dollar amount of medical aid payments; industry of claimant;
county of claimant; ANSI z16.2 codes for body area; nature;
and type of disorder, number of claims filed by the claimant
between 1991 and 1998, and whether the claimant received a
surgical procedure related to CTS. Claim costs and time-loss
days reported here reflect actual totals for closed claims. For
claims that were not closed, costs and time-loss days reflect
actual totals paid through January 1999 plus total future
estimated costs and time-loss days, as calculated by agency
case reserve staff.
Claimant Earnings Profiles
A total of 9,305 claims were identified in the State Fund
database. The quarter in which the claim was filed divides
time into ‘‘pre-injury period’’ and ‘‘post-injury period’’ for
each claimant. These claimants were linked by social
security number (SSN) to their quarterly earnings records
as reported by their employers to the Washington State
Employment Security Department (ESD), which manages
unemployment insurance. ESD collects information on
wages and hours worked per quarter for each employee in
the state. In this way, quarterly earnings profiles for the
9,305 claimants were assembled, beginning with the first
4 More than 98% of ‘‘compensable’’ CTS claims involve four or more lostworkdays; however there are a small number of cases where no time-lossdays are incurred.
5 Selecting a control group of workers without any claims from theEmployment Security Department’s reported earnings database would beunsatisfactory because these records do not indicate the worker’s genderor age, which are important predictors of earnings.
158 Foley et al.
quarter of 1990 and continuing through the fourth quarter of
2001. To reduce the loss of claimants from the database due
to retirement, and to focus on workers having pre-injury
earnings records in the ESD database, workers whose age at
time of injury was under 16 or over 70 were excluded.
Claimants with no reported earnings in the quarter of injury
were also excluded, as this quarter is used as a benchmark to
compare to post-injury earnings. Finally, to ensure that any
earnings impact observed is not related to some other work-
related injury, we excluded those claimants with any previous
lost-time claim from 1990 up to the first claim for the
target condition in the study period. These exclusions
together yielded 8,760 earnings records available for study:
4,443 CTS claimants, 2,544 fracture claimants, and 1,773
claimants with medical-only dermatitis. Calendar quarters
were converted to quarters before/after the quarter of injury
to define time elapsed since injury when looking across
claimants injured in different calendar quarters. All earnings
were converted into year 2001 dollars using the National
Urban Wage Earners Consumer Price Index. In addition to
providing claimants’ quarterly earnings, ESD wage records
provided information on the claimants’ employer at the
time of injury. This included the total employment of the
establishment as well as the four-digit standard industrial
classification (SIC) code. Finally, this database allows one to
track breaks in the claimants’ employment history over the
40 quarters of the study period.
When a claimant has no reported earnings for a given
quarter, these were treated as having zero earnings. It is
recognized that in some cases these claimants may have
simply left Washington State but are working elsewhere, or
they may have taken jobs not covered by unemployment
insurance, or they may have become self-employed. Due to the
natural turnover in the labor market a proportion of any set of
workers who all have earnings records in any given index
quarter, will have earnings records in adjacent quarters that
will decline the further away from the index quarter one looks,
either forward or backward in time. Since a worker’s absence
from the ESD wage records is regarded as their having zero
earnings for that quarter, the time-profile of the cohort’s
median earnings slopes downwards as one moves in either
direction away from the index quarter. This would be true even
for a set of uninjured workers. In the case of the three injury
cohorts, approximately 20% of these workers have no reported
earnings in the fourth quarter prior to their quarter of injury.
The downward slope after injury is thus due both to natural
labor force turnover (e.g., retirement, self-employment, and
out-migration) and to the effect of injury preventing their
return to work. Thus the median earnings profiles presented
below are likely underestimates of the true earnings of these
claimants. Nevertheless, they do focus on the comparative
change in earnings between those of the group whose injuries
are relatively minor—the medical-only claimants—and those
of the groups whose injuries caused them to lose four or more
days from work and to receive wage-replacement benefits—
the time-loss or ‘‘compensable’’ claims. Reasons for leaving
employment that are unrelated to injury may vary system-
atically across the three injury cohorts. To isolate the
independent impact of the injury on CTS claimants’ earn-
ings, we controlled for the variation in worker characteristics
which might be related to the probability of their leaving
formal employment separately from the impact of their
injury. In this way the excess loss of earnings of the CTS
cohort over that of either fractures or dermatitis claimants is
seen as an indication of the economic burden of CTS.
Multivariate Analysis
In order to detect the independent contribution of injury
type to long-term economic burden, post-injury earnings as a
percent of pre-injury earnings level were modeled on the set
of predictors described in Table II.
Using linear regression, the following model was
estimated:
LOGðYYR6=YPREÞ ¼ aþ b1 � INJURYTYPE þ b2 � AGE
þ b3�EMPLOYERSIZE þ b4�SEX
þ b5�AGE � SEX þ b6�SECTOR
þ b7�REGION þ b8�PRESTABLE
In this model YYR6/YPRE is the individual worker’s ratio
of average quarterly earnings in the year beginning 6 years
after the quarter of injury to that of average quarterly earnings
in the year prior to injury. Claimants with less than $100 in
average quarterly earnings in the year prior to their injury
were dropped from this model.6 For each variable in the
model, the group expected to have the highest post-injury
earnings recovery is used as the reference category. These
are: dermatitis, youngest age group, male, large employer,
fixed-site industry, Puget Sound region, and stable pre-injury
employment history. Other worker characteristics may also
be expected to affect the time profile of their earnings, but
were unavailable for inclusion in the model, such as
education level, race, or occupation. But since each worker’s
earnings in the sixth year post-injury is taken into the model
as a fraction of their own earnings level in the year prior to
their injury, this makes each worker serve as their own-
matched control, which helps to compensate for the missing
variables. Although only the results from the model at 6 years
post-injury are presented, this model was also fitted for 1 and
3 year(s) post-injury in order to see whether the predictors
retain the same approximate impacts on earnings recovery
and these results are discussed below.7
6 Since earnings in period YYR6 could be zero, we adjusted these claimants’earnings recovery fraction from 0 to 0.0001 prior to the log-transformation.
7 ‘‘Sixth year post-injury’’ is defined as quarters 25–28 after the quarter ofinjury; ‘‘3 years post-injury’’ means quarters 13–16; ‘‘1 year post-injury’’includes quarters 5–8.
Long-Run Economic Burden of CTS 159
In addition to this model each possible two-way
interaction between predictors was tested whose main effect
was statistically significant at the 6-year point. For each
interaction statistical significance was determined by com-
paring the model as shown above with a model including
all of these terms plus the additional interaction (such as
injury type and age category). Of all the possible two-way
interactions that might be added to the model above, only two
(age category by injury type and age category by pre-injury
employment stability) were statistically significant at the
0.05 level. None of the interactions were statistically
significant at the more conservative 0.01 level. With 20
possible two-way interaction terms available beyond the
age� gender interaction already included, the risk of a false
positive is high, so the number of interactions in the model
presented in Table V-a was limited to the only one that was
statistically justified.
In addition, a logistic regression model of the probability
of having a surgery was fitted as a function of CTS subgroup,
pre-injury earnings category, age group, sex, employer size,
sector, region, and pre-employment stability.
Cumulative Earnings Loss
The multivariate regression model outlined above
estimates the impact of injury type on post-injury earnings
recovery, at 6 years post-injury, for CTS claimants relative to
fractures and dermatitis claimants. This estimate controls for
the impact of differences across injury cohorts in age, gender,
size of employer and other predictors. Similarly, to portray
the cumulative earnings loss of the whole CTS cohort over 1,
3, and 6 years post-injury, the difference in earnings recovery
was compared across the three injury cohorts by fitting the
multivariate regression model to each post-injury quarter
separately. For each CTS case the individual’s income loss
attributable to CTS relative to either fracture or dermatitis
was calculated. In order to estimate the loss for each post-
injury quarter T, a multivariate linear regression model for the
log ratio of post-injury income at quarter T and pre-injury
income was fitted. The following model was used.
LRATIOT ¼ LOGðYT=YPREÞ ¼ aT þ b1T
� FRACTURE þ b2T�CTS þ b3T
� AGE25�34þb4T � AGE35�39þb5T
� AGE50þ þ b6T�EMPLOYERSIZESMALL þ b7T
� EMPLOYERSIZEMEDIUMþb8T
� SEX þ b9T�AGE25�34 � SEX þ b10T
� AGE35�39 �SEX þ b11T�AGE50þ�SEXþb6T
� SECTOR þ b7T�REGION þ b8T
� PRESTABLE þ e
where YT is the observed income in the post-injury quarter T
and YPRE is the mean observed income in the year prior to
injury. To estimate the loss attributable to CTS in quarter T
the individual’s estimated income was calculated as if they
had had a fracture instead of CTS (denoted by YTjFRAC).
YTjFRAC was calculated from the above multivariate
model as
YTjFRAC¼YT exp½PREDðLRATIOTjFRACÞ�PREDðLRATIOTÞ�¼YT exp½b1T�b2T�
where PRED(LRATIOTjFRAC) and PRED(LRATIOT) are
predicted values from the multivariate linear regression for
quarter T. PRED(LRATIOTjFRAC) is the individual’s pre-
dicted value using all of their covariate values as they are,
TABLE II. Definitions of Predictors Used inMultivariate Analysis
Variable Definition
INJURYTYPE Type of injury (CTS, fracture, or dermatitis)CTSGROUP Subgroup of CTS claimants (specific, augmented, or other)AGE Age of the claimant at time of claim; categories are16^24, 25^36, 37^49, and 50 or overEMPLOYERSIZE Size of the claimant’s employer asmeasured by employment; categories are1^10,11^49, 50 or overa
SEX Gender of claimantSECTOR Claimant worked in a fixed-site or non-fixed site industry; non-fixed industry includes construction and transportation; all other industries are
considered fixedREGION Geographic location of claimant’s place of employment; categories are: the Puget Sound area (King, Pierce, Snohomish,Thurston, and Kitsap
counties) and non-Puget sound area (all other counties)PRESTABLE Indicateswhether claimant had earnings in all sixquarters prior to the quarter of claimSURGERY Indicateswhether CTS claimant had either a carpal tunnel release surgery or an arthroscopic procedurePREINJURYEARNINGS Categorizeseachclaimantby their averageearningsover the fourquartersprior to theirquarterofclaim; categoriescorrespondto thequartiles
of the earnings distribution: Less than $2,743; $2,743^$5,093; $5,093^$7,748; and $7,748 andmore
aTests failed to reject the null hypothesis that a fourth size category (200 or more) was no different from the category 50^200 employees, so these were combined.
160 Foley et al.
but changing injury type from CTS to fracture. PRE-
D(LRATIOT) is the individual’s predicted value using all of
their covariate values as they are and keeping the injury type
as CTS. The estimated quarterly loss LOSSTjCTS-FRAC is the
difference between the observed income YT and YTjFRAC.
The individuals’ quarterly estimated losses were then
summed over all post-injury quarters and individuals to
provide a total estimate of excess earnings loss for the CTS
group during the periods of 1, 3, and 6 years following the
quarter of injury.8
All dollar amounts are expressed in year 2001 values,
and losses were discounted at 3% per year so that they are in
present value form at the time of injury. All statistical
analyses were carried out in SAS, version 9.1, and in the
statistical language R, version 2.01.
RESULTS
Demographic and employment-related characteristics
of claimants vary substantially when they are grouped by
injury type (see Table III). Compared with either fractures or
dermatitis claimants, CTS claimants tend on average to be
older, to be more steadily employed—defined as having
reported earnings in six out of six quarters prior to the quarter
of injury, and are more likely to be female. A disproportio-
nately greater number of CTS claimants reside in the Puget
Sound area of Washington State (defined as King, Pierce,
Snohomish, Thurston, and Kitsap counties) than either of the
other injury cohorts; and they tend to have higher pre-injury
earnings than do claimants in the other cohorts. Pre-injury
earnings also decline as one moves across the three CTS
subgroups: $5,404 for Group 1, $4,646 for Group 2, and
$4,587 for Group 3. Claimants with fractures are more likely
to work in ‘‘non-fixed site’’ industries—typically construc-
tion and transportation—and to work for smaller employers.
They are also the group with the highest proportion of males.
The claimants with dermatitis were the youngest, were most
likely to work for a large, fixed-site employer, and had the
lowest pre-injury earnings of the three cohorts. There was a
great deal of overlap in the industries in which claimants
worked across the three injury cohorts: six of the top eight
industries in both fractures and dermatitis show up in the
top eight for CTS. But there was a noticeable difference in
ranking among the top five for each: fractures tended to occur
more in the non-fixed site industries (e.g., construction and
transportation), while health care and retail trade played a
bigger part in both CTS and dermatitis cases. By two-digit
standard industrial code (SIC) the top five industries for
fractures are: SIC 17 (construction-trades), SIC 15 (con-
struction-residential); SIC 24 (sawmills and logging); SIC 01
(agriculture); SIC 58 (restaurants). These account for 40% of
the total cases. By two-digit SIC code the top five industries
for CTS are: SIC 17 (construction-trades), SIC 58 (restau-
rants); SIC 80 (health care); SIC 54 (grocery stores); and SIC
24 (sawmills and logging). These account for about 30% of
the total. By two-digit SIC code the top five industries for
dermatitis are: SIC 58 (restaurants); SIC 01 (agriculture);
SIC 80 (health care); SIC 17 (construction-trades); and SIC
51 (wholesale trade-non-durable). These account for 40% of
the claims. For the three CTS groupings there was no
difference in industry composition: by two-digit SIC the
three subgroups overlapped each other by 70%–90%, with
SIC 58, 17, and 80 appearing in the top four in all three
subgroups.
TABLE III. Characteristics of Claimants by InjuryType
Carpal tunnelsyndrome Fractures
Dermatitis(med-only)
Total claimants 4,443 2,544 1,773Percentmale 43% 84% 62%Median age 38 34 30Percent Puget sound 58% 54% 49%Percent fixed industry 73% 66% 85%Percent large firm 54% 44% 62%Percent with pre-injury earnings stability 66% 55% 52%Median pre-injury quarterly earnings $5,032 $4,116 $3,438Median earnings as percent of pre-injury level: Year1a 69.6% 102.3% 95.2%Median earnings as percent of pre-injury level: Year 3a 62.3% 103.1% 94.1%Median earnings as percent of pre-injury level: Year 6a 52.9% 98.4% 83.3%
aYear1is quarters 5^8 after the quarter of injury; Year 3 is13^16 quarters after injury; Year 6 is 25^28 quarters after the quarterof injury.
8 One-year loss estimate used quarters 1–4 post-injury; 3-year estimateused quarters 1–12; 6-year estimate used quarters 1–24.
Long-Run Economic Burden of CTS 161
Time-Loss Duration
Since the length of time a claimant is not able to work
following injury is a significant factor in determining their
long-run earnings, the issue of time-loss was examined in
more detail for the two time-loss injury categories: CTS and
fractures. In particular, we looked at the distribution of time-
loss by injury type and other demographic characteristics to
see whether time-loss varied systematically with other
potential predictors of long-run earnings. It should be noted
that time-loss days is not a measure of time elapsed from
injury until return to work. It simply measures days of State
Fund paid time-loss incurred while the claim is still open.
As Table IV shows, workers with CTS claims are on time-
loss far longer than are those with fractures. Within the CTS
cohort the distribution of time-loss shifts to progressively
longer and longer duration when comparing Group 1 to either
Group 2 or Group 3. Those CTS claimants who undergo a
carpal tunnel surgical procedure have about a 30% longer
period of time-loss than those who do not have a surgery, with
most of this difference concentrated among claimants in
Group 1. There is a stronger age-related increase in time-loss
duration for the CTS cases than is true of the fractures, except
for the oldest age cohort. Although women account for a
larger fraction of CTS cases than men, it is the men who tend
to remain on time-loss status longer. There is no significant
difference by sex for duration of time-loss among the fracture
cases. Large differences in time-loss duration also appear for
TABLE IV. Time-Loss Days Paid to Claimants, by Demographic Characteristics and OtherAspects of the Claim and Claimant
Cases Median time-loss days paid
NCTS NFRAC
By injury typea
CTS 4,443 138Fracture 2,544 46
NCTS NFRAC All cases Caseswith surgery Caseswithout surgeryBy CTS categorySpecific* 2,123 101 105 74Augmented* 1,044 165 182 154Other* 1,277 238 228 256
Cases Median time-loss days paid
NCTS NFRAC CTS Fracture
By age group16^24 years old* 359 621 109 4325^36 years old* 1,539 888 144 4237^49 years old* 1,860 689 145 5150^70 years old 685 346 127 64
By sexMale*b 1,909 2,136 155 45Female*,b 2,534 408 122 46
Bypre-injury stabilityContinuous* 2,945 1,402 113 42Non-continuous* 1,498 1,142 197 50
By industry sectorAll other* 3,247 1,670 123 42Construction andtransportation*
878 841 188 55
By employer size200þworkers*,b 1,174 413 107 4250^199workers*,b 1,240 701 130 3911^49workers*,b 1,216 849 165 511^10workers 813 581 162 51
*Differences between categories are statistically significant at the 5% level.aTable excludes dermatitis claims because these were all medical-only claims by design.bSignificant for CTS cases only.
162 Foley et al.
both CTS and fractures cohorts between those with
continuous employment history before their injuries and
those with sporadic employment histories. For both CTS
and fractures, the median duration of time-loss post-injury is
longer for those who are employed in the construction and
transportation industries than it is for those employed in
fixed-site industries such as manufacturing, retail, or
services. The relative increase in time-loss is substantially
larger for CTS cases than for the fractures. Finally, there is a
clear, inverse relationship between the size of the employer
and the median length of time-loss for both injury cohorts.
The beneficial impact of employer size on time-loss is far
greater for CTS cases than it is for fractures.
Earnings Recovery
Figure 1 shows median quarterly earnings, as a percent
of earnings in the quarter of their claim, for each cohort. This
is tracked for the forty-quarter period starting three years
prior to the quarter of injury and continuing for 7 years post-
injury. Looking at how these earnings profiles differ by injury
illustrates the impact of the injury in a way not easily
appreciated by means of the multivariate models alone
because it shows how the deficit in earnings among CTS
claimants evolves over time. Earnings for the CTS cohort are
broken out into the three subgroups discussed above
(‘‘specific,’’ ‘‘augmented,’’ and ‘‘other’’) because large and
statistically significant differences develop between them.
Earnings for all cohorts except dermatitis are similar
prior to the quarter of injury. However, earnings post-injury
follow distinctly different tracks across the injury types. The
earnings of the dermatitis cohort only gradually decline,
probably due to natural labor market exit as discussed above.
The story is similar for the compensable fractures cases.
While their earnings decline sharply for the first quarter post-
injury, due to their temporary disability, they return to more-
than-full earnings beginning with the second post-injury
quarter. After that, their earnings fraction gradually declines,
but they retain the highest fraction of pre-injury earning
power of any of the injury cohorts. For the CTS group, the
post-injury course of earnings is sharply different. All three
CTS subgroups lose a much larger share of their pre-injury
earnings than is the case with the dermatitis or fractures
groups. And there is no obvious post-injury recovery after a
short-term disability, as with the fractures. CTS Group 1
earnings stabilize at roughly 60% of the pre-injury level after
1 year. For the ‘‘augmented’’ CTS subgroup the loss of
earnings is greater: their median earnings fall to roughly
30% of pre-injury levels before stabilizing. Finally, for CTS
Group 3, the most broadly defined category of CTS case,
earnings fall continuously and approach zero within roughly
3 years after the claim is filed.
Another important predictor of earnings recovery for the
CTS claimants is whether or not they undergo surgery to
relieve pressure on the median nerve. Figure 2 shows the
earnings profiles for the CTS claimants broken out by
‘‘surgery’’ versus ‘‘no surgery.’’ Out of all claimants with a
CTS designation, 55.4% received a carpal tunnel release
procedure. About 1.4% received an arthroscopic procedure.
These proportions varied by whether the claimant was
classified as a CTS case by upper-extremity specific ANSI
codes or by an ICD-9 code alone. In particular, 77.2% of the
‘‘CTS specific’’ group underwent a carpal tunnel release
procedure; the corresponding proportion for the other two
FIGURE 1. Medianquarterlyearningsaspercentof injuryquarter.
Long-Run Economic Burden of CTS 163
subgroups was 43.3% for the ‘‘CTS augmented’’ group and
40.1% for the ‘‘CTS other’’ group. As Figure 2 shows, the
earnings outcomes for CTS claimants who underwent
the carpal tunnel release procedure were strikingly better
than for those who did not have the surgery even though they
had more time-loss. It should be noted that the claimants who
did not receive surgery had significantly lower earnings prior
to their CTS claim than did those who went on to have the
surgery. In Group 1 the median pre-injury earnings of those
claimants who went on to have surgery was $5,664 versus
$4,542 for those who did not. Similar differences were found
in Groups 2 and 3. But as Figure 2 shows even when
controlling for this difference, the earnings gap widens after
the injury. In the logistic regression model it was found
that higher pre-injury earnings was positively associated
with having surgery (OR¼ 1.44; 95% confidence interval
1.14–1.83) even when controlling for CTS subgroup, age
group, sex, employer size, sector, region, and pre-employ-
ment stability in the model. Older claimants were more
likely to have surgery (over age 50: OR¼ 3.03; CI 2.44–
4.10). Females were less likely to have surgery
(OR¼ 0.73; CI 0.62–0.85). No relationship was found
between the size of the claimant’s employer, pre-injury
employment stability, or industry sector and likelihood of
having surgery.
Earnings profiles for claimants with CTS also varied by
gender when comparing fixed-site employment to non-fixed-
site employment. As Figure 3 shows, male claimants with
CTS show a marked difference between those working in
fixed-site industries and those working in non-fixed
site industries, with males in non-fixed industries doing
especially poorly. For females with CTS there is no such
inter-sector difference.
Multivariate Analysis
Based upon the results presented in the earnings charts
and in the univariate descriptive analysis above, a variety of
multivariate model specifications were tested over various
time periods. The underlying hypothesis is that those
claimants with carpal tunnel syndrome suffer a greater loss
in their ability to return to work at full earnings following
injury as compared to claimants with either an upper
extremity fracture or a medical-only dermatitis claim.
However, several other factors are included which may be
important in determining both the level and trend of
an individual’s earnings over time: gender, age, the
differing demands of working in non-fixed-site industries
such as construction, the size and region of the employer, and
the worker’s own history of work stability prior to injury.
Studying the recovery of earnings allows us to isolate the
impact of injury on the worker’s ability to resume their full
productive potential after they have returned to work. Once
again the critical comparison to be made is the impact of CTS
on the recovery of earnings as compared to that of the other
two injury types. The model was run for three post-injury
periods: 1 year, 3 years, and 6 years post-injury. Since the
primary interest is the long-term economic impact of CTS,
only the results for earnings 6 years after the quarter of injury
are reported in Table V-a. However, results for all three post-
injury time periods are discussed below.
FIGURE 2. ImpactofsurgeryonCTSmedianquarterlyearnings.
164 Foley et al.
The multivariate regression results accord well with
those seen in the univariate tables: at 6 years post-injury,
claimants with CTS have much poorer outcomes than do
claimants with either fractures or dermatitis. CTS claimants
recover only 45% of their pre-injury earnings level as
compared to the rate of recovery for dermatitis claimants
(exp[coefficient]¼ 0.45; CI 0.34–0.59, P< 0.001). The
same model, estimated at 1-year and 3-years post-injury,
shows that for CTS claimants there is evidence of a greater
initial impact of the injury on earnings, followed by a gradual,
and partial, recovery relative to the other two cohorts. One
year after claim filing, their relative earnings recovery (RER)
is 0.29 (0.23–0.36) as compared to dermatitis; at 3 years
this relative recovery is 0.35 (0.27–0.45). Other predictors
with significant negative impacts on earnings recovery are:
older age, smaller-size employer, working in a non-fixed
industry sector, working outside of the Puget Sound region,
and having an unstable pre-injury employment history. The
age effect is less pronounced at 1 year and 3 years post-injury
than it is at 6 years. For all age groups other than the youngest
the RER declines with time after injury. The deficit grows
particularly for workers over age 50: falling from an RER of
FIGURE 3. A: Females with CTS: median earnings by fixed-site or non-fixed-site Industry.B: Males with CTS: median earnings by
fixed-site ornon-fixed-site industry.
Long-Run Economic Burden of CTS 165
0.47 at 1 year post-injury to 0.18 at 3 years and 0.07 at 6 years.
For workers aged 16–24, males have substantially better
earnings growth 6 years post-injury than do females (0.59;
0.36–0.98). However, this advantage disappears for workers
between the ages of 25 and 49, for whom there is no
statistically significant, or substantive, difference between
males and females. Female workers aged 50 and over recover
their earning power much more successfully than do older
males (2.58; 1.52–4.39).
The age-gender interaction changes as workers
are considered at 1, 3, and 6 years post-injury. Whereas at
the 1-year point no statistically significant difference are
found across the four age groups between males’ and
females’ earnings recovery, a pattern emerges at the 3-year
mark that shows younger males doing better as compared to
young females, and females over 50 doing better than males
over 50. By the 6-year point, this pattern is even more
entrenched.
One three-way interaction, age by gender by injury type,
was found to be statistically significant at the 6-year post-
injury point, though it was not included in the model depicted
in Table V-a because its inclusion does not change the injury
group impacts on earnings. Instead, this interaction is more
easily seen by examining how the age–gender interaction
terms vary when the same regression model is fitted to each
injury cohort separately (CTS, fractures, and dermatitis).
Each injury cohort shows the same pattern of age by gender
effects as shown in Table V-a: older workers recover less than
younger workers, and the gender differential consistently
shows that younger males recover more earning power
than younger females, while older females recover more than
older males. Only the magnitude of the age-gender interac-
tion effect differs across the three injury cohorts: the gradient
of the age-gender differential is steeper for CTS than for
either the dermatitis or fractures cohorts.
Given the size of the earnings recovery deficit for
workers with CTS over age 50, the question is raised whether
the earnings recovery estimate for CTS at 6 years is driven
mainly by the collapse of earning power for the older age
group. The model in Table V-a was re-estimated excluding all
workers over 50 and only a small change was found in
estimated earnings recovery from that of the fully populated
model: the CTS recovery fraction rises from 0.45 to
0.51 relative to dermatitis claimants.
Although not all results of all possible interaction terms
are reported, because their inclusion in the model does not
substantively change the magnitudes of the injury recovery
ratios, there were statistically significant interactions
between age and injury type which were consistent with
the univariate results: older workers did relatively worse in
each injury category than did younger workers, and older
workers with CTS had the lowest earnings recovery. In both
CTS and fractures there was a substantial loss of earnings
among workers over age 50 relative to those of workers over
50 with dermatitis. However, the loss for CTS claimants was
about 30% greater than for fractures.
The interaction of sex and industry sector showed that
males in the construction and transportation sectors fared
worse relative to males in the fixed-site sector (�25%).
Females in the construction and transportation sectors
showed a similar deficit (�16%) relative to their counterparts
in the fixed-site sector, but this difference was not statistically
significant, perhaps due to the small numbers of female
claimants in the non-fixed sector.
It was expected that a significant difference would be
found between how males and females would fare across the
different injury types. But when an interaction term for sex
and injury type was included in the model, the results did not
support this: there was no significant interaction between sex
and injury type.
Finally we tested whether workers’ earnings recovered
differently across injury types between the fixed and non-
fixed industry sectors.9 Across all injury types workers in the
non-fixed sector had poorer long-term earnings recovery. But
the deficit in earnings recovery for CTS claimants in the non-
fixed sector, at 35% relative to CTS claimants in the fixed
sector, was three times larger than it was for workers with
fractures or dermatitis. In addition, this deficit was the only
one that was statistically significant.
The recovery pattern is potentially dependent on yet
higher order interactions (three-way and higher), yet this
sample size, though very large, is not sufficient to reliably
decide among the possibilities. Clearly the role of age and
gender and their combination, plus their combination with
other factors is important, as also indicated by the discussion
above of various age or gender interactions. All of these
three-way interactions involving age and gender give results
consistent with those in Table V-a, though the magnitudes of
the effects vary somewhat. Thus, Table V-a fairly represents
the effect of the variables considered, and some more
variations on the theme may be discovered with considerably
larger sample sizes.
Sub-Groups of CTS Claimants
The income recovery model was re-estimated for the
CTS claimants only, broken out by CTS sub-group, to see
whether there were systematic differences between the three
sub-groups in their recovery of their pre-injury earnings
levels and to examine the impact of having a carpal tunnel
release surgery. Table V-b has the results of this model. All of
the predictors from Table V-a retain their signs and
approximate magnitudes, and only the impact of subgroup
and surgery is discussed here.10
9 ‘‘Non-fixed’’ industry sector refers to the construction and transportationindustries.
10 For space reasons, therefore, we have omitted all but these predictorsfrom Table V-b.
166 Foley et al.
TABLE V-a. Multiple RegressionModel of Relative Earnings Recovery as a Function of InjuryType, Demographics,Region and Industry Predictors, 6 Years Post-Injury
Variable CategoryRelative earnings
recoveryLower 95%
CIUpper 95%
CIGlobalPP-value
Injury type <0.001CTS 0.45 0.34 0.59Fractures 0.85 0.64 1.14Dermatitis 1.00 Reference category
Agea <0.00150 and over 0.07 0.05 0.1035^49 0.57 0.42 0.7725^34 0.68 0.51 0.9124 and under 1.00 Reference category
Sexa 0.6Female 1.06 0.85 1.32Male 1.00 Reference category
Female compared to maleby age at injury
<0.001*
50 and over 2.58 1.52 4.3935^49 1.03 0.72 1.4525^34 0.98 0.68 1.4024 and under 0.59 0.36 0.98
Size of employer 0.02Small 0.72 0.55 0.94Medium 0.79 0.63 0.99Large 1.00 Reference category
Sector 0.03Non-fixed 0.75 0.59 0.97Fixed 1.00 Reference category
Region <0.001Non-Puget 0.61 0.50 0.74Puget 1.00 Reference category
Pre-injury employment <0.001Non-stable 0.39 0.32 0.48Stable 1.00 Reference category
aMarginal effects of age and sex from the model without the age-sex interaction.*P-value for the interaction of age and sex.
TABLE V-b. Multiple RegressionModel of Relative Earnings Recovery as a Function of CTS Subgroup and SurgeryStatus
Variable Category Relative earnings recovery Lower 95%CI Upper 95%CI PP-value
CTS group Group 3 0.52 0.37 0.74 <.0001Group 2 0.72 0.51 1.04 0.08Group1 1.00 Reference category
SurgeryNo 0.62 0.46 0.83 0.002Yes 1.00 Reference category
Six years post-injury: estimates adjusted for age, gender, age-gender interaction, employer size, sector, Puget/non-Puget, stable/non-stable variables. CTS claimants only.
Long-Run Economic Burden of CTS 167
Claimants in CTS Group 3 have much poorer long-term
outcomes than do claimants with more specifically defined
CTS codes. As before, other predictors with significant
negative effects on recovery of earnings are: older age,
smaller-size employer, working in a non-fixed industry
sector, working outside of the Puget Sound region and having
a sporadic pre-injury employment history. In addition,
claimants who had a carpal tunnel release surgery experi-
enced much better earnings recovery at the 6-year mark. The
effect of surgery on earnings recovery did not vary
significantly across the three CTS subgroups.
These results raise the question whether the deficit in
earnings recovery for CTS claimants is driven mostly by the
performance of CTS Groups 2 and 3. The model was then
restricted to CTS Group 1, fractures and dermatitis claimants.
The results parallel those of Table V-a in that all predictors
retain their signs and levels of significance as before.
Claimants in CTS Group 1 do relatively better than CTS
claimants as a whole, as compared to the fractures and
dermatitis claimants. However, they still show a substantial
shortfall in their earnings recovery at 6 years post-claim
relative to that of the other two injury type groups: 38% less
recovery than that of dermatitis claimants and nearly 20%
less recovery than that of the fractures cohort. If the analysis
is restricted to the CTS Group 1 claimants who had surgeries
we find they recover about 31% less of their pre-injury
earnings after 6 years as do the dermatitis claimants
(P< 0.03).
A regression model was also estimated in which the total
number of days of paid time-loss at claim closure was a
function of the same set of predictors in the same form as used
in the earnings recovery model, with the single addition of
pre-injury earnings level as a predictor. Dermatitis claimants
were not included in this model as they had no days of paid
time-loss. All claims were closed prior to the 6-year
measurement point, so no further accumulation of paid
time-loss occurs with these claims after the time of the
analysis. As with the earnings recovery model all claimants
are present and included in the analysis, whether or not they
have returned to work. The results of this model support the
hypothesis that claimants with CTS experience a substan-
tially greater burden than do claimants with upper extremity
fractures: controlling for other predictors, their time-loss was
more than 300% longer for CTS than for fractures
(exp[coefficient]¼ 4.36; CI 3.96–4.80; P< 0.0001). Other
impacts also accorded with the earnings recovery model:
older workers, employees of smaller businesses and those
working in the construction or transportation sectors had
longer periods of time-loss following their claims. Time-loss
was slightly less for women than for men. Geographic region
and pre-injury employment stability were not associated with
length of time-loss. Finally, claimants’ length of time-loss
was inversely related to their pre-injury earnings level, with
each successively higher income quartile having shorter
time-loss than the one below it. Claimants in the highest pre-
injury earnings quartile have about half the time-loss as those
in the lowest quartile.11
In addition to its impact on time-loss we also tested
whether pre-injury earnings level predicted long-term earn-
ings recovery. Since pre-injury earnings forms the denomi-
nator of the dependent variable in the model tested above, it
could not be included directly in the model. But median
earnings recovery percentages at 6 years broken out by injury
type and pre-injury earnings quartile show that, for CTS and
fractures, those with the highest pre-injury earnings also have
higher rates of earnings recovery than those with lower pre-
injury earnings. This is especially true for CTS claimants,
with 64.8% earnings recovery for the highest quartile versus
23% recovery for the lowest quartile. There is a smaller, but
still notable difference for the fractures claimants (87%
recovery for the highest earning group vs. 62% for the
lowest). For the dermatitis cohort there is not a substantive
difference between the highest earning claimants and those in
the third quartile. However, for this group the lowest pre-
injury earnings quartile actually had the highest rate of
earnings recovery after 6 years, at 156% of pre-injury levels.
This may be related to this group’s younger age composition
as well as the minimal impact of their illness.
Perhaps the best summary measure of the overall
difference in the burden suffered by CTS claimants relative
to fractures and dermatitis claimants is the difference in
cumulative long-term earnings losses. This is presented in
Table VI. If CTS claimants’ post-injury earnings had
followed the same trajectory of recovery as did those of
fractures or dermatitis claimants, controlling for differences
across injury cohorts in the covariates, they would have
earned between $197 million and $382 million more than
they did over a 6-year period after injury. On a per claimant
basis, this is an average of between $45,762 and $88,894 in
cumulative lost earnings over the 6-year period. Further-
more, as a comparison of the disparity at 1, 3, and 6 years
11 We used ordinary least-squares (OLS) regression analysis to determinethe association of time-loss duration to injury type, controlling for theother predictors. While the data on duration could also have beenanalyzed using survival analysis methods, the OLS regression approachis preferable for several reasons. First, none of the individual workers’time-loss durations were censored. Second, the OLS model compares theactual duration of time-loss across different categories of workers.Survival analysis, by contrast, is well suited for comparing the risk(hazard ratio) of an event between categories of claimants. For these datathe event in question would be the end of the time-loss period. But such acomparison is of less interest to this study than the relative length oftime-loss duration across injury types. Since the end of time-loss does notnecessarily imply an immediate or successful return to work, comparingearnings losses is a better method for measuring the impact of injury.Nevertheless, a survival analysis using a Cox proportional hazardsregression model was performed to estimate the likelihood of the end oftime-loss as a function of injury type, with sex, age, pre-injury earningsstability, and level of pre-injury earnings as covariates, using PROCPHREG in SAS v9.1. This model estimated a hazard ratio for fracturesrelative to CTS of 0.432 (CI: 0.408–0.457, P< 0.0005). So at a givenpoint in time, the hazard of a fractures claim reaching the end of time-loss status in the workers’ compensation system was about 2.3 timeshigher than that for a CTS claim.
168 Foley et al.
shows, the deficit continues to grow over time. There is no
evidence of any convergence of earnings.12
DISCUSSION
The main finding of this analysis is that CTS claimants
return to a much lower fraction of their pre-injury earnings
than do claimants with either medical-only dermatitis or lost-
time upper extremity fractures, and they endure much longer
periods of time-loss than do claimants with upper extremity
fractures. These results remain even when controlling for
other predictors of time-loss or earnings. CTS claimants
experience more than three times as much time-loss as
claimants with fractures. Six years after filing the claim, the
average fraction of pre-injury earnings achieved by the CTS
cohort is less than half that of the dermatitis claimants, and
about 45% below that of the fractures cohort. These
differences capture only the gap in take-home earnings
between the cohorts. Any excess loss of fringe benefits by the
CTS cohort is not included in this comparison, but can be
expected to amplify the shortfall. Part of this deficit may
be related to the length of time which elapses from onset of
symptoms to treatment. Those with CTS are less likely to
seek immediate treatment compared to fractures. It should be
kept in mind, however, that the term ‘‘time-loss’’ only
captures the number of days for which the claimant received
wage replacement payments from L&I. Any time lost prior to
the start of wage replacement benefits payments is not
captured. If the claimant has subsequent interruptions in
their employment due to an inability to handle their
customary tasks, this is also not captured by this measure
unless the claim is re-opened and wage replacement
payments resume. A better overall measure of economic
impact, which incorporates the impact of post-closure breaks
in employment, is the long-term quarterly earnings of the
claimant measured at 6 years after the claim is filed.
The number of lost workdays for the set of CTS cases
analyzed in this study is much higher than that which is
reported in the Bureau of Labor Statistics (BLS) Survey of
Occupational Injuries and Illnesses, based upon surveyed
OSHA 300 employer logs. Whereas the CTS cases involve
between 101 and 238 days of paid time-loss, BLS lost
workday cases have a median of about 32 lost workdays in
2003. This disparity also appears for upper extremity
fractures: the set of time-loss workers’ compensation claims
have a median of 46 days of paid time-loss. The median lost
workdays for upper extremity fractures cases reported by the
BLS was only 10. This may be due to several reasons. First,
unlike the set of workers’ compensation claims, BLS cases
are based upon employer reports and may include a wide
range of hand/wrist conditions not medically diagnosed as
carpal tunnel syndrome. Second, BLS cases include those
with only 1–3 lost workdays, whereas State Fund time-loss
claims must involve at least 4 lost workdays. Third, the self-
insured employers were excluded from this analysis.
Because of their larger size, they tend to offer more
opportunities for early return to work. Fourth, the BLS
Survey reports days away from work only up to 1 year
following the injury event, while claims can still accumulate
lost days more than 1 year post-injury. Finally, it is possible
that, in order for a worker to be willing to take on the cost in
unreplaced wages and perhaps the stigma of filing a workers’
compensation claim, their case must first develop to a more
severe stage, with positive electrodiagnostic findings, result-
ing in more lost workdays than is the case with the reports
surveyed by the BLS [Azaroff et al., 2002].
A second result is that those CTS claimants with specific
ANSI codes which originally define CTS as the primary
injury have better earnings recovery and shorter time-loss
than those with only a diagnosis code on one of their medical
bills consistent with CTS. This may be a function of the
claims administration system. When a claim is first
processed, the ANSI coding is based upon the primary
condition of the claimant, for example, ‘‘nerve condition
affecting the wrist.’’ If this specific ANSI code is not present
it may indicate that the primary condition is unrelated to
CTS, or it may mean that the case is more complicated and
takes longer to diagnose and treat. The interval from the date
of injury reported on the claim to the date a medical provider
first makes a diagnosis of CTS ranges across the three
subgroups from a median of 14 days for Group 1, to 71 days
for Group 2, and to 133 days for Group 3. Once diagnosed,
however, there is no variation across the subgroups in the
interval from diagnosis until surgery. This interval is about
135 days for all subgroups. The presence of a CTS-related
ICD-9 code on one of many medical bills for a claimant may
indicate an acute traumatic event such as a fall from elevation
or a motor vehicle crash, where CTS is only one part of
a complicated case requiring more recuperation time.
However, lengthier recuperation may also result from a
12 If we restrict the CTS cohort just to Group 1, the subset whose claimswere classified early in the case history as being related specifically to thewrist or hand area by ANSI z16.2 codes, we find a per claimantcumulative loss of between $22,125 and $50,727 over the 6 year post-injury period.
TABLE VI. Cumulative ExcessMean Earnings Loss for CTS ClaimantsCompared to Fracture and Dermatitis Claimants
Periodelapsed
CTS relative to fractures CTS relative to dermatitis
Per claimant Group Per claimant Group
One yeara $12,821 $55,105,855 $22,143 $95,172,460Three yearsa $31,374 $134,847,030 $49,800 $214,038,515Six yearsa $45,762 $196,685,843 $88,894 $382,065,630
aIn this table post-claim time periods were defined as follows: ‘‘One Year’’¼quarters1^4; ‘‘ThreeYears’’¼quarters1^12; ‘‘Six Years’’¼quarters1^24.
Long-Run Economic Burden of CTS 169
lack of prompt diagnosis and treatment of CTS, or may
raise issues of appropriate or timely claim administration.
An analysis of the relationship between length of time-
loss and delays in claim processing, as measured by the
length of time taken to pass certain significant claims
administration landmarks (such as date of assignment of
employer liability, date of first time-loss payment, and date of
surgery) might reveal significant opportunities to improve
long-term worker outcomes. Inadequate treatment due to
delayed identification and poor claim administration lead to
substantially greater morbidity for CTS claimants [Daniell
et al., 2005].
It was also found that males with CTS who work in
non-fixed industries, such as construction or transportation
fare less well than workers in any other gender-industry
combination. Both the construction and transportation
industries are predominantly male. The heavy manual work
often involves vibration and hand-intensive tasks. Many jobs
also involve skills acquired over many years of employment.
When these skills are compromised by CTS, it may be much
more difficult to return to work than in other industries.
Another factor potentially hindering recovery of earning
potential is that construction is comprised disproportionately
of small firms, with an average of about 7 employees as
compared to the all-industry average of about 15 employees
per firm. These employers may believe they do not have the
light duty positions available which would be appropriate for
a recovering worker. In general, the size of employer is
inversely related to time-loss and recovery of earnings. Large
employers tend to have a greater diversity of work positions
available so accommodation of the worker may be easier
during the recuperation period. Because self-insured
employers were excluded, the analysis of CTS earnings
recovery among workers employed by large firms is missing
those working for some of the very largest employers in
Washington State. This also means that we were unable to
examine whether differences in cost incentives for employers
who self-insure may alter their policies so as to accommodate
workers’ return to work earlier than is seen among those
employers in the State Fund, independently of employer
size.
Differences in treatment of CTS may also account for
part of the variation in length of time-loss and earnings.
CTS claimants who had carpal tunnel release surgery had
better earnings outcomes than those who did not have
surgery. This is in spite of the fact that CTS claimants who
underwent surgery had longer periods of time-loss than those
without surgery, even when controlling for CTS subgroup.
This does not, by itself, indicate that more CTS claimants
should be getting surgeries. It may be that those CTS
claimants who have surgery represent less complicated,
more definitive cases, such as those having a positive
nerve conduction velocity (NCV) test, which is required
in Washington State, where treatment is relatively
straightforward.13 This is supported by the finding that
CTS claimants with specific ANSI codes for CTS as their
primary condition are much more likely to have surgery. An
implication of this finding is that early reporting and NCV
testing may lead to better earnings outcomes. However, it is
not known what time-loss or earnings recovery for claimants
in the CTS surgery group would have been had they not had
surgeries.
The large relative loss of earnings for the non-surgery
CTS cases as compared to the surgery CTS cases and the
fractures and dermatitis cohorts may indicate that workers
without some visible signs of injury or illness are more likely
to experience long delays in obtaining proper recognition of
their condition and appropriate treatment. The fact that this
group also tends to have lower pre-injury earnings levels may
also indicate that members of this group are less able or
willing to overcome any barriers to reporting their disorders
promptly, perhaps for fear of lost wages, job loss, or
discrimination.
There is no information in this dataset about what, if any,
ergonomic improvements have been made to accommodate
the CTS claimants’ return to work. Nor is it known if they
return to the same or to a different job. Variation in employer
accommodation is believed to play an important role in
preserving workers’ long-term earnings potential.
High pre-injury earnings are associated with shorter
time-loss and better return to pre-injury earnings levels. They
are also associated with a higher probability of receiving a
carpal tunnel release surgery even when controlling for CTS
subgroup and industry sector. One reason for this difference
may be that high-wage workers are harder to replace, so
employers press for quick treatment and are more likely to
make necessary accommodations to keep them working as
compared to unskilled, lower wage workers. High pre-injury
earnings levels may also denote higher levels of education
and greater comfort or experience with reporting symptoms
of ill health to physicians. Higher income workers also may
press for early return because for them the fraction of pre-
injury earnings that are replaced by workers’ compensation
payments is lower than it is for lower wage workers. A lack of
access to health care resources and paid sick leave benefits,
which are not uncommon among the lower wage working
population, could lead some workers to avoid reporting their
CTS symptoms until the severity of their condition is
relatively high.
Earnings recovery and time-loss also varied system-
atically with demographic and economic characteristics of
workers. The chances for successful recovery of earnings are
13 In the Washington State workers’ compensation system’s AttendingDoctor’s Handbook, there have been specific criteria since 1993 forallowing carpal tunnel surgery, including positive electrodiagnosticfindings. Prior to this, surgery was sometimes conducted without meetingclinical guidelines. The prevalence of surgery usage among CTSworkers’ compensation cases can be expected to vary across the UnitedStates and other countries.
170 Foley et al.
much poorer for older workers across all injury types,
especially for workers over age 50. This, together with the
result that older workers face much longer time-loss, sup-
ports recent findings that older workers who are injured face
higher risk for early retirement than uninjured older workers
[Pransky et al., 2005]. In addition, the recovery of earnings
varies by gender across age groups: younger males do better
than younger females; but older females do better than older
males. Several questions are raised by this last result: are
older males more likely to be eligible to receive Social
Security Disability Insurance payments? For older males
with CTS, are their cases more severe by the time they file
claims? Do they develop the disorder working in occupations
in which it is more difficult to accommodate their return to
work in their accustomed jobs? Earnings recovery was better
for workers in large firms and in the fixed industry sector.
Workers with unstable pre-injury employment histories did
have more trouble recovering their earning potential,
although this was not due to enduring longer periods of
time-loss. Also unlike time-loss, earnings recovery did differ
significantly by region: workers in the Puget Sound area had
much better success recovering to their pre-claim earning
potential than did workers outside of this urbanized region.
This could be related to the long-standing differential across
Washington State in labor market conditions. The Puget
Sound area typically enjoys lower unemployment rates and
higher average wages than other areas of the State. The
opportunities to find alternative occupations more suited to
workers’ post-injury capacities may be better in the much
denser labor market of the Puget Sound region.
We also tested whether the direct relationship between
higher pre-injury earnings and better long-term earnings
recovery varied by injury type. The result was clear: higher
pre-injury earnings made a much bigger difference to long-
term earnings recovery for CTS than it did for either fractures
or dermatitis. It is evident that some combination of
employee accommodation, early diagnosis and appropriate
treatment is associated with higher wage workers, allowing a
much better long-term outcome than is the case for lower
wage CTS claimants. For fractures and dermatitis claimants
there is evidently less room for these other factors to affect
claimants’ probability of successful return to work.
Finally, when controlling for differences in demographic
and other income predictors across the three injury types, the
cumulative excess loss of earnings of the 4,443 CTS
claimants included in this study amounted to between $197
million and $382 million over the 6-year period post-injury
for which data were collected, a per claimant earnings loss of
between $45,000 and $89,000 compared to workers with
fractures or dermatitis, respectively. These losses are similar
in magnitude to those reported in other studies for the most
seriously disabling injuries [Reville et al., 2001]. Wage
replacement payments partially and temporarily cushion the
burden of this loss to individual workers during the period in
which their claims are open. But from society’s perspective
this loss is a lower bound estimate of the full burden, since it is
based upon a comparison to two cohorts of workers who are
themselves recovering from injuries rather than upon a
comparison to an uninjured control population. Moreover,
the cumulative loss measured at 6 years is likely to be much
smaller than lifetime cumulative loss, since annual losses
remained large even at the end of this period. Because median
age at injury was only 38 for the CTS cohort, a potentially
large proportion of the lifetime earnings loss is not captured
here. Even so, these losses are very large when compared
with the direct cost of a CTS claim as measured only by State
Fund medical costs and wage replacement payments: the
median total direct cost per claim for CTS in the State Fund
over the period 1993–2001, as reported by L&I was $5,235
[Silverstein et al., 2003].14 Finally, there is no evidence that
the gap in earnings between CTS claimants and workers with
fractures or dermatitis converges as time passes.
The losses of CTS claimants compared to those of
fractures claimants, also raises the issues of differences in
injury visibility, reporting, and timeliness of treatment. This
would suggest that policies are needed which favor primary
prevention through ergonomic assessment and job improve-
ment, and which encourage the early reporting of hand/wrist
symptoms such as numbness and tingling before progression
of the disorder leads to clinical CTS and long-term loss of
work ability.
CONCLUSION
The reported cost of a workers’ compensation claim
reflects only a part of the full burden of a work-related injury
or illness. A portion of this burden falls on the employer in the
form of indirect costs to replace the injured worker. On the
workers’ side the burden can take many forms, both
economic and social. The focus of this study was on the
workers’ long-term loss of earnings. The results show that
long-term earnings losses far exceed the reported direct costs
of CTS claims: their cumulative excess loss of earnings
amounted to between $197 million and $382 million over the
6 years following the claim, a loss of between $45,000 and
$89,000 for each CTS claimant in the study. Because the
losses captured by this study only cover 6 years following
injury, lifetime cumulative loss is likely to be much larger,
since annual losses were still quite large at the end of
this period and median age at injury was only 38. CTS
claimants recover to a much lower fraction of their pre-injury
earnings than do claimants with either dermatitis or upper
extremity fractures, and they endure much longer periods of
time-loss than do claimants with upper extremity fractures.
Given the magnitude of these uncompensated losses, and
the devastating effect they can have on workers and their
14 In 2001 dollars.
Long-Run Economic Burden of CTS 171
households, this study points to the need for a renewed
emphasis on primary prevention, early reporting and diagno-
sis, appropriate treatment, and assistance for employers to
accommodate an early and successful return to work.
ACKNOWLEDGMENTS
Michael Foley and Barbara Silverstein conducted this
research while employed by the Washington State Depart-
ment of Labor and Industries. We acknowledge the
invaluable statistical assistance of Blazej Neradilek. Edmund
Rauser provided programming help. We thank Randy Clark
and two anonymous referees for their thoughtful reviews and
comments.
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