bringing the media in: newspaper readership and human rights
TRANSCRIPT
Rights*
Bringing the Media in: Newspaper Readership and HumanRob Clark, University of Oklahoma
Socio
� 20
DOI:
Cross-national studies examining human rights outcomes have seldom considered
the role of the news media. This is unfortunate, as a large body of work in media stud-
ies suggests that the news industry effectively educates citizens, shapes public attitudes,
and stimulates political action. I juxtapose these two literatures in a cross-national con-
text to examine the print media’s impact on a state’s human rights performance. First,
examining micro-level evidence from the World Values Survey, I show that an individ-
ual’s level of media consumption, including newspaper readership, is positively associ-
ated with participation in human rights organizations. Next, I present macro-level
evidence regarding the aggregate effect of a society’s newspaper readership on its
human rights record. Analyzing an unbalanced dataset with a maximum of 459 obser-
vations across 138 countries covering four waves during the 1980–2000 period, I use
ordered probit regression to examine the relationship between a state’s newspaper read-
ership and its Amnesty International rating. I find that newspaper readership exerts
strong, positive effects on a state’s human rights practices net of other standard predic-
tors and temporal ⁄ regional controls. Moreover, the effect of readership is robust to a
number of alternative specifications that address concerns with ceiling effects, measure-
ment bias, influential observations, sample composition, mediation, endogeneity, and
the impact of alternative forms of media consumption (i.e., the Internet and television).
Introduction
Previous cross-national studies have linked a state’s human rights perfor-
mance to a number of domestic and international factors (Hafner-Burton and
Tsutsui 2005; Poe, Tate, and Keith 1999). However, less attention has been
directed toward the potential role of the news media in shaping a state’s
human rights performance. In theory, the news media occupy a critical posi-
tion in society. The media industry is responsible for educating citizens and
disseminating important information. Journalists function as state monitors and
corporate watchdogs, holding private and public institutions accountable for
their actions. In addition, media outlets serve as venues that foster public dis-
course where citizens can exchange ideas, form opinions, and take appropriate
action. In sum, the news media represent important monitors of societal
operations.
logical Inquiry, Vol. xx, No. x, 2012, 1–25
12 Alpha Kappa Delta
10.1111/j.1475-682X.2012.00417.x
2 ROB CLARK
The news industry may also play an active role in monitoring human
rights activities of the state. Research suggests that international media cover-
age is highly responsive to human rights conditions across the world (Ramos,
Ron, and Thoms 2007). In fact, human rights have become an increasingly
salient theme in media coverage over the past several decades. Between 1982
and 1994, Reuters World Service increased its human rights coverage by 500
percent, while the British Broadcasting Corporation’s Summary of World
Broadcasts experienced a 600 percent increase over the same period (Ron
1997). And between 1986 and 2000, Newsweek increased its human rights
coverage by 100 percent, while the Economist increased its coverage by 300
percent (Ramos, Ron, and Thoms 2007). More importantly, past research sug-
gests that media exposure has the capacity to shape attitudes and behavior
with respect to human rights. One study surveying the attitudes of African
women toward female genital cutting found that media exposure negatively
affected a woman’s attitude toward female circumcision and reduced the odds
that these women would circumcise their daughters (Boyle, McMorris, and
Gomez 2002).
In this study, I fill a notable gap in the literature by assessing the print
media’s impact on a country’s human rights performance. First, I review pre-
vious studies that demonstrate the newspaper industry’s capacity to educate
citizens, shape their attitudes, and mobilize them to become politically active.
Next, using data from the World Values Survey, I examine micro-level evi-
dence linking media consumption to human rights activities, showing that two
survey items (regularly reading a daily newspaper and actively following the
news on television, radio, or daily newspapers) are positively associated with
participation in human rights organizations net of controls. Finally, I present
analyses of macro-level data that show the positive impact of newspaper read-
ership on a country’s human rights record. I conclude by underscoring the
importance of the news media in empowering citizens to monitor and regulate
state behavior.
Media Studies
The Impact of Newspapers
A number of empirical studies have documented a range of empowering
effects that the news media has had on citizens. First, the industry is generally
regarded as a popular source for acquiring knowledge. ‘‘The most regularly
used information source, by virtually all accounts, is the mass media, espe-
cially television and the press’’ (Dalton, Beck, and Huckfeldt 1998:111). In
particular, several early studies provided initial support for the idea that
newspaper exposure positively predicts knowledge. One study found that
NEWSPAPER READERSHIP AND HUMAN RIGHTS 3
individuals living in communities with more daily newspapers were able to
identify more problems facing their state (or the country) than individuals
living in areas with fewer newspapers (Chaffee and Wilson 1977). Another
early study found that political coverage in newspapers positively predicts the
number of reasons individuals are able to give for supporting one political
candidate over another (Clarke and Fredin 1978). Since that time, other
research has shown that newspaper reading positively affects political
knowledge (Kleinnijenhuis 1991; Nicholson 2003; Pattie and Johnston 2003).
In addition, newspapers have the capacity to shape public opinion and
mobilize readers into political action. Newspaper exposure stimulates different
forms of political participation, such as attending a political meeting, writing a
letter to the editor of a newspaper, television, or magazine, contacting an
elected official, working for a political campaign, or circulating a petition
(McLeod and McDonald 1985; McLeod, Scheufele, and Moy 1999). In fact,
newspaper reading has been shown to positively affect voter turnout among
young adults (Bybee et al. 1981).
Extending this line of research to other media forms, studies have also
examined the impact of television news on viewers. However, researchers gen-
erally conclude that newspaper reading yields far greater returns than televi-
sion viewing, and there are strong theoretical reasons for believing so. First,
television consumers have less control over the pace at which information is
digested. Thus, not surprisingly, experimental research has shown that individ-
uals are able to recall news stories presented in print more easily than those
presented through television or radio (DeFleur et al. 1992). And, second, tele-
vision news provides considerably less information than newspapers. Televi-
sion broadcasts feature fewer words and ideas per news story than appear in a
front page newspaper article (McLeod, Scheufele, and Moy 1999:321; Robinson
and Davis 1990:109).
A number of empirical studies have shown that newspaper readers are
better informed than television viewers. Several studies have found that news-
paper reading positively predicts political knowledge with an effect about
twice as large as TV news viewing (Kwak 1999; McLeod, Scheufele, and
Moy 1999). In other research, reading newspapers significantly increases
knowledge and awareness of political issues, while watching TV news does
not (Robinson and Davis 1990; Scheufele, Shanahan, and Kim 2002). In addi-
tion, research suggests that newspapers better equip citizens with knowledge
of political candidates (Becker and Dunwoody 1982). Past research has shown
that reliance on newspapers for political information significantly increases a
voter’s ability to discriminate between candidates on specific issues, while
reliance on television, radio, and magazines for political information does not
(Berkowitz and Pritchard 1989).
4 ROB CLARK
Moreover, studies find that exposure to newspapers produces more active
citizens than exposure to TV news. For example, several studies find that the
effect of newspaper reading on political knowledge and participation is nota-
bly stronger than that of watching television news (McLeod and McDonald
1985; Scheufele, Shanahan, and Kim 2002). And yet another study reports that
newspaper reading positively predicts political knowledge, voting behavior,
and overall political participation, while TV news viewing has no significant
impact on any of these outcomes (Eveland and Scheufele 2000). Finally, in a
study of university students, exposure to print media was a better predictor of
political knowledge and participation (e.g., voting, demonstrating, participation
in political meetings and discussion) than exposure to TV news (Feldman and
Kawakami 1991). In sum, these studies suggest that it is important to distin-
guish between television and newspapers when considering the capacity for
the news media to educate citizens, shape public sentiment, and stimulate
political action. Thus, in this study, I investigate the mobilizing impact of the
newspaper industry. Specifically, I examine whether the print media can effec-
tively trigger social change in one of the most important sectors of govern-
ment activity at the cross-national level: human rights practices.
Generalizability
However, one reason for skepticism is that most of the above studies
were conducted within the United States, possibly leading one to draw conclu-
sions about the print media’s efficacy that may not be warranted in different
societal contexts. Interestingly, though, the positive effects of media consump-
tion on the mass public do emerge elsewhere. Comparative studies covering
European nations have linked media exposure to knowledge (Curran et al.
2009; Kleinnijenhuis 1991; Pattie and Johnston 2003). And one study conducted
in Japan shows that exposure to, and reliance on, print media for political infor-
mation positively predicts political knowledge and participation (Feldman and
Kawakami 1991). These findings have even been extended to the developing
world. For example, in Mali, exposure to television and radio news positively
predicts political knowledge (e.g., correctly naming political incumbents),
while exposure to newspaper and radio news positively predicts political par-
ticipation (e.g., attending a community meeting, demonstration, or election
rally, working for a political candidate or party, or signing a petition) (Nisbet
2008).
Analytic Strategy
To demonstrate the link between a country’s newspaper industry and its
human rights performance, I present evidence in two stages. Because
the impact of the print media theoretically operates at the micro-level, it is
NEWSPAPER READERSHIP AND HUMAN RIGHTS 5
important to first establish an empirical connection at the level of the individ-
ual (stage one) prior to addressing the primary research question regarding the
macro-level impact of newspaper readership on human rights practices (stage
two). Thus, I first examine micro-level evidence linking media consumption to
participation in human rights organizations. Prior studies have shown that
news media exposure, especially print media, leads individuals to become
more politically active. Accordingly, I examine whether individuals that read
daily newspapers and follow television or radio news are more likely to join
human rights organizations. I then shift to my primary analyses, examining
macro-level evidence linking newspaper readership at the societal level to a
country’s human rights practices. At the aggregate level, I expect the cumula-
tive effect of print media exposure to significantly improve a country’s human
rights record.
Micro-Level Evidence
If exposure to the news media has a mobilizing effect on the citizenry in
the area of human rights, we should expect to see evidence of this at the indi-
vidual level. In this section, I draw from data covering several waves of
the World Values Survey (2006) to examine whether media consumption is
Table 1Membership in Human Rights Organizations by Media Consumption
Membership in human
rights organizations
Regularly read a daily newspaper?
Wave: 1981–1984
0 = No 1.36% (79 of 5,792)
1 = Yes 2.62% (356 of 13,572)
Follow news on television, radio, or daily papers?
Wave: 1999–2004
1 = Never 1.78% (112 of 6,292)
2 = Less often 2.60% (329 of 12,664)
3 = Once or twice a week 2.66% (249 of 9,374)
4 = Several times a week 3.04% (470 of 15,444)
5 = Every day 4.16% (1,422 of 34,180)
Source: World Values Survey (2006).
6 ROB CLARK
positively associated with participation in human rights institutions. Table 1
presents two questionnaire items. Both items are behavioral questions, asking
respondents to indicate (1) whether they regularly read a daily newspaper (i.e.,
four of every six issues) (asked during the 1981–1984 survey wave), and (2)
how often they follow politics in the news on television, the radio, or daily
newspapers (asked during the 1999–2004 survey wave). I organize the
responses to these items according to whether or not these same individuals
reported belonging to a human rights organization. As Table 1 indicates, those
who regularly read newspapers were about twice as likely (2.62%) to report
being a member of a human rights organization as those who were not regular
readers (1.36%). Similarly, those who reported following the news more fre-
quently on television, radio, or newspapers were progressively more likely to
participate in a human rights organization, ranging from ‘‘never’’ following
the news (1.78% participation rate) to following the news ‘‘every day’’ (4.16%
participation rate). In sum, these results suggest that media consumption in
general, and newspaper readership in particular, is positively associated with
participation in human rights activities.
In Table 2, I examine whether these differences across levels of media
consumption are statistically significant, net of controls, using a set of probit
models. All models include a set of country dummies (results not reported to
preserve space) and are estimated with robust standard errors. Models 1–3
consist of respondents from 16 Western countries from the 1981–1984 wave
of the World Values Survey, while models 4–6 consist of respondents from a
broader set of 24 countries from the 1999–2004 wave. Because different coun-
tries participate in different survey waves, and exposure to specific survey
items may vary across both country and wave, the resulting samples for these
models are different. Prior to analyses, I standardized all predictors (mean = 0;
standard deviation = 1) so that the reported coefficients allow interested read-
ers to compare the magnitude of each variable’s effect. Thus, each cell reports
the standardized coefficient with the robust standard error in parentheses. After
estimating the focal predictors in isolation, I add controls for each respon-
dent’s gender, age, education, and income (both education and income are
ordinally coded as low, medium, and high). In addition, I include three rele-
vant attitudinal measures, including (1) an item that asks respondents to evalu-
ate their country’s level of respect for individual human rights, ranging from
‘‘a lot of respect’’ (low) to ‘‘no respect at all’’ (high), (2) an item that asks
respondents whether they think human rights policies should be left to national
governments to decide for themselves (low), decided by national governments
with coordination from the United Nations (middle), or handled exclusively by
the United Nations (high), and (3) an item that asks respondents to indicate
which geographic group they belong to most: locality, region, country,
Ta
ble
2P
rob
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od
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ge
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rs)
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12
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=lo
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=h
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NEWSPAPER READERSHIP AND HUMAN RIGHTS 7
Ta
ble
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on
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)
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ery
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**
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01
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(.0
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).1
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tes
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15
,96
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No
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exic
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ldo
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ilip
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uth
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ica,
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uth
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ain
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zan
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sts)
.
8 ROB CLARK
NEWSPAPER READERSHIP AND HUMAN RIGHTS 9
continent, or the world. I dichotomize this last item into ‘‘world versus other’’
(world = 1). Models from the earlier survey wave do not include controls for
education and the attitudinal measures because of missing data.
Overall, these models indicate that media consumption is a positive pre-
dictor of participation in human rights activities. Specifically, model 1 shows
that newspaper readership positively predicts membership in a human rights
organization, and this relationship persists net of the controls introduced in
models 2 and 3 (I add a second-order polynomial for age in model 3, as the
elderly may participate less actively than the middle-aged). Similarly, model 4
shows that media consumption, more generally, is a positive predictor of
human rights activity, and this association holds net of a larger set of controls.
In sum, these models suggest that media consumption is a significant predictor
of membership in human rights organizations. Thus, the descriptive patterns
identified in Table 1 hold up in a multivariate context, as revealed by the anal-
yses presented in Table 2.
Interestingly, there is some indication that these human rights practices at
the micro-level may be linked to human rights outcomes at the societal level.
For example, among the Western countries featured in models 1–3 above,
their average level of participation in human rights organizations during the
1981–1984 period is positively associated with their human rights record (as
measured by their Amnesty International rating) during the 1980–1985 period
(r = .520). Western countries that featured a perfect Amnesty rating of 5 dur-
ing this period had an average participation rate in human rights organizations
of 2.8 percent, while those with an Amnesty rating of <5 only had an average
participation rate of 1.2 percent. In sum, this suggests that the impact of media
exposure on human rights activities at the micro-level may translate into the
news media’s broader impact on a country’s human rights record.
Macro-Level Evidence1
Dependent Variable
Amnesty Rating. Data on human rights practices come from Hafner-
Burton and Tsutsui (2005), who update existing data based on their content
analysis of human rights reports, using an inverted standards-based ordinal
Political Terror Scale. As they note, scores range from 1 to 5, with a score of
1 indicating ‘‘systematic repression,’’ 2 indicating ‘‘extensive repression,’’ 3
indicating ‘‘widespread repression,’’ 4 indicating ‘‘limited repression,’’ and 5
indicating ‘‘rare repression’’ (for a more detailed description, see Hafner-Burton
and Tsutsui 2005:1392). Separate scores, based on annual reports from Amnesty
International (AI) and the U.S. State Department (USSD) are available. The
USSD tends to rate its allies, trading partners, and foreign aid recipients more
10 ROB CLARK
favorably than AI, and rates leftist regimes relatively more harshly (Poe, Carey,
and Vazquez 2001). Therefore, I rely primarily on the AI version. However, I
follow previous studies that ‘‘blend’’ the two (e.g., Poe, Tate, and Keith 1999),
primarily using AI, and relying on the USSD when AI ratings are not available.
Despite potential bias in the U.S. State Department ratings, the AI and USSD
scores that come from Hafner-Burton and Tsutsui (2005) are highly correlated
(r = .840) and have become increasingly similar over time (Poe, Carey, and
Vazquez 2001). In most cases, there is no difference between the two scores,
and in only 4 percent of cases do the scores differ by more than one point (Poe,
Carey, and Vazquez 2001:659). Of the 459 cases in my base sample, I rely on
USSD ratings for only two observations: Gabon (wave 4) and Norway (wave 4).
Moreover, when I exclude these two cases from the analyses, the results are
quite similar (see Table 4, model 3).
Independent Variable
Newspaper Readership. I measure each country’s daily newspaper
readership using circulation rates for newspapers published at least four times
a week, calculated as average circulation (or copies printed) per 1,000 people.
Data come from the United Nations Educational, Scientific, and Cultural Orga-
nization (UNESCO) Institute for Statistics, as made available in the WorldDevelopment Indicators (International Bank for Reconstruction and Develop-
ment 2004). Newspaper circulation is generally regarded as a conservative
measure of readership because each copy is read by more than one person on
average. In the United States, readership is on average about 2.3 times larger
than daily circulation (World Association of Newspapers 2007). For example,
the Chicago Tribune, Los Angeles Times, and Washington Post average over
two readers per copy, while USA Today averages over three readers per copy,
and the New York Times averages over four readers per copy (Audit Bureau of
Circulations 2009; World Association of Newspapers 2007). These readership
levels are comparable with those achieved by major newspapers in other
advanced countries, such as Germany and Ireland (World Association of
Newspapers 2007). And when considering less developed countries, circulation
figures tend to be even more conservative estimates of readership, as news-
papers in these countries typically have higher ‘‘pass-on’’ rates (World
Association of Newspapers 2007).
Technical Controls
I estimate the effect of newspaper readership net of the following techni-
cal controls.
NEWSPAPER READERSHIP AND HUMAN RIGHTS 11
Amnesty Rating (lagged value). I include the lagged value of the
dependent variable so that I can more appropriately measure the impact
of readership on change in a state’s human rights performance.
Time Period. I also control for longitudinal change in Amnesty scores
across the sample period by including time period as a predictor in the analy-
ses (1980–1985 = 1; 1985–1990 = 2; 1990–1995 = 3; 1995–2000 = 4).
World Region. In addition, I control for cross-sectional variation in
Amnesty ratings by including world region as a predictor in the analyses. I
classify states as belonging to one of the six world regions shown in Table 3,
with Europe and the West serving as the excluded reference category.
Substantive Controls
I also include a broad set of substantive predictors, many of which have
been used in prior human rights research. First, I control for institutional and
societal features that may shape the role and impact of the news media. For
example, it is possible that the news industry may only serve as a critical and
independent monitor of societal operations when media outlets enjoy substan-
tial autonomy and ⁄ or when they are situated within democratized nations. In
authoritarian states, the government may own or control the media and attempt
to influence public opinion by deliberately distorting or excluding information
that is disseminated to the public, and ⁄ or remaining silent on (or diverting
attention away from) particular issues (Ojo 2003). Moreover, previous work
suggests that the ability for a free press to positively impact a country’s
human rights performance is restricted to those states that are fully democratic
(Whitten-Woodring 2009). In addition, the capacity for the news media to
effectively inform and mobilize the citizenry may depend on how educated
these populations are. For example, previous studies have shown that the posi-
tive effects of media consumption and newspaper reading on political knowl-
edge are greater among highly educated individuals (Kleinnijenhuis 1991;
Nisbet 2008). Consequently, it is important to control for a country’s level of
press freedom, democracy, and formal education when estimating the impact
of the newspaper industry on its human rights practices.
Press Freedom. Data on press freedom come from Whitten-Woodring
(2009) who transforms Van Belle’s (1997) ordinal measure on media freedom
by dichotomizing states into two groups: (1) those states with a ‘‘free media,’’
and (2) those states with a ‘‘government-controlled media’’ (Whitten-Woodring
2009:607). Van Belle’s measure covers the 1948–1995 period. All states des-
ignated as having ‘‘free media’’ throughout the 1980–1995 period (for which
Ta
ble
3R
egio
nal
Pat
tern
san
dL
on
git
ud
inal
Tre
nd
sin
New
spap
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ead
ersh
ip
19
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–1
98
51
98
5–
19
90
19
90
–1
99
51
99
5–
20
00
Ch
ang
e(%
)
All
stat
es(N
=1
26
)9
9.8
29
9.9
49
9.6
09
7.3
8)
2.4
4
Eu
rop
e&
the
Wes
t(N
=2
3)
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1.1
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.25
27
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54
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)1
2.4
8
Lat
inA
mer
ica
&th
eC
arib
bea
n(N
=2
6)
86
.40
83
.76
82
.10
81
.48
)5
.69
Cen
tral
&su
b-S
ahar
anA
fric
a(N
=3
8)
12
.22
11
.13
10
.40
11
.37
)6
.96
No
rth
Afr
ica
&th
eM
idd
leE
ast
(N=
20
)6
7.7
57
2.0
58
2.9
69
0.8
33
4.0
7
Eas
tA
sia
&th
eP
acifi
c(N
=1
9)
95
.55
98
.70
10
3.4
71
07
.47
12
.48
Eas
tern
Eu
rop
e&
Cen
tral
Asi
a(N
=2
3)
––
12
4.3
01
13
.23
)8
.91
No
tes:
Eu
rop
e&
the
Wes
t=
Au
stra
lia,
Au
stri
a,B
elg
ium
,C
anad
a,C
yp
rus,
Den
mar
k,
Fin
lan
d,
Fra
nce
,G
reec
e,Ic
elan
d,
Irel
and
,It
aly
,L
ux
emb
ou
rg,
Mal
ta,
Net
her
lan
ds,
New
Zea
lan
d,
No
rway
,P
ort
ug
al,
Sp
ain
,S
wed
en,
Sw
itze
rlan
d,
Un
ited
Kin
gd
om
,U
nit
edS
tate
s;L
atin
Am
eric
a&
the
Car
ibb
ean
=A
rgen
tin
a,B
aham
as,
Bar
bad
os,
Bo
liv
ia,
Bra
zil,
Ch
ile,
Co
lom
bia
,C
ost
aR
ica,
Cu
ba,
Do
min
ican
Rep
ub
lic,
Ecu
ado
r,E
lS
alv
ado
r,G
uat
emal
a,G
uy
ana,
Hai
ti,
Ho
nd
ura
s,Ja
mai
ca,
Mex
ico
,N
icar
agu
a,P
anam
a,P
arag
uay
,P
eru
,S
uri
nam
e,T
rin
idad
-To
bag
o,
Uru
gu
ay,
Ven
ezu
ela;
Cen
tral
&su
b-S
ahar
an
Afr
ica
=A
ng
ola
,B
enin
,B
ots
wan
a,B
urk
ina
Fas
o,
Bu
run
di,
Cam
ero
on
,C
had
,C
on
go
(DR
),C
on
go
(R),
Eq
uat
ori
alG
uin
ea,
Eth
iop
ia,
Gab
on
,G
amb
ia,
Gh
ana,
Gu
inea
-Bis
sau
,Iv
ory
Co
ast,
Ken
ya,
Les
oth
o,
Lib
eria
,M
adag
asca
r,M
alaw
i,M
ali,
Mau
riti
us,
Mo
zam
biq
ue,
Nam
ibia
,N
iger
,N
iger
ia,
Sen
egal
,S
ierr
aL
eon
e,S
om
alia
,S
ou
thA
fric
a,S
ud
an,
Sw
azil
and
,
Tan
zan
ia,
To
go
,U
gan
da,
Zam
bia
,Z
imb
abw
e;N
ort
hA
fric
a&
the
Mid
dle
Eas
t=
Afg
han
ista
n,
Alg
eria
,B
ahra
in,
Eg
yp
t,
Iran
,Ir
aq,
Isra
el,
Jord
an,
Ku
wai
t,L
eban
on
,L
iby
a,M
oro
cco
,O
man
,P
akis
tan
,Q
atar
,S
aud
iA
rab
ia,
Sy
ria,
Tu
nis
ia,
Tu
rkey
,
Un
ited
Ara
bE
mir
ates
;E
ast
Asi
a&
the
Pac
ific
=B
ang
lad
esh
,B
run
ei,
Fij
i,In
do
nes
ia,
Jap
an,
Lao
s,M
alay
sia,
Mal
div
es,
Mo
ng
oli
a,M
yan
mar
,N
epal
,N
ort
hK
ore
a,P
apu
aN
ewG
uin
ea,
Ph
ilip
pin
es,
Sin
gap
ore
,S
ou
thK
ore
a,S
riL
ank
a,T
hai
lan
d,
Vie
tnam
;E
aste
rnE
uro
pe
&C
entr
alA
sia
=A
lban
ia,
Arm
enia
,A
zerb
aija
n,
Bel
aru
s,B
osn
ia-H
erze
go
vin
a,B
ulg
aria
,C
roat
ia,
Cze
chR
epu
bli
c,E
sto
nia
,H
un
gar
y,
Ky
rgy
zsta
n,
Lat
via
,L
ith
uan
ia,
Mac
edo
nia
,M
old
ov
a,P
ola
nd
,R
uss
ia,
Ser
bia
-
Mo
nte
neg
ro,
Slo
vak
ia,
Slo
ven
ia,
Taj
ikis
tan
,U
kra
ine,
and
Uzb
ekis
tan
.
12 ROB CLARK
NEWSPAPER READERSHIP AND HUMAN RIGHTS 13
data are available) are coded as one (i.e., those states with press freedom)
throughout the sample period, while those states designated as having ‘‘gov-
ernment-controlled media’’ during any part of the 1980–1995 period are coded
as zero (i.e., those states without press freedom).2
Democratization. Democracy scores come from Marshall and Jaggers
(2005) Polity IV project that provides longitudinal political regime characteris-
tics for countries. I use their combined polity score, which is computed by
subtracting a state’s autocracy score from its democracy score. Scores range
from )10 to 10.
Tertiary Education. I measure each state’s level of formal education by
their tertiary school enrollment, which refers to the proportion of people in the
age group that officially corresponds to the tertiary level who are currently
enrolled.
In addition to the above measures, previous studies reveal a number of
other domestic forces that impact a state’s human rights record. For example,
state repression is more likely to occur within nations that suffer from under-
development, civil war, and ⁄ or population pressures (Hafner-Burton and Tsutsui
2005; Poe, Tate, and Keith 1999). Previous studies have also considered the
importance of international linkages, focusing on international participation in
treaties, organizations, and trade (Hafner-Burton and Tsutsui 2005). Thus, I
also control for a broad set of domestic and international factors that may
influence human rights practices.
GDP PC (PPP) (log). Gross domestic product per capita is based on
purchasing power parity. Data are in 1995 international dollars. An interna-
tional dollar has the same purchasing power over GDP as the U.S. dollar
has in the United States.
Civil War. Civil war is a dummy variable, referring to the presence or
absence of ‘‘intra-state war’’ in each state during each wave of the sample
period. Data come from Sarkees (2000) Correlates of War project (version
3.0).
Population Density (log). Population density refers to a country’s popu-
lation divided by its land area in square kilometers. Population estimates are
based on all residents regardless of legal status or citizenship (except for refu-
gees not permanently settled in the country of asylum) who are generally con-
sidered part of the population of their country of origin.
14 ROB CLARK
Treaty Ratifications. Following Hafner-Burton and Tsutsui (2005:
1394), I consider a state’s ratification of six human rights treaties, along with
two optional protocols that are designed to (1) enhance monitoring and
enforcement, and (2) eliminate the death penalty. In total, this measure refers
to the number of human rights instruments a state has ratified by the end of
each wave, with scores ranging from 0 to 8 across the sample period. Data
come from the Office of the United Nations High Commissioner for Human
Rights (http://www.ohchr.org).
International Organizations (log). International organizations refer to
the sum of conventional international governmental organizations and interna-
tional non-governmental organizations to which each country belongs, listed in
sections A–D of the Yearbook of International Organizations (Union of Inter-
national Associations). Data for each wave come from single years: 1980,
1985, 1990, and 1995.
Trade Openness (log). Trade openness refers to the sum of exports and
imports of goods and services, measured as a share of gross domestic product.
Analysis
Following Hafner-Burton and Tsutsui (2005), I estimate ordered probit
models of the ordinal dependent variable (Amnesty International rating) on the
independent variables. Also, adhering to Hafner-Burton and Tsutsui’s (2005)
methodology, I address potential heteroskedasticity by clustering on states.
Thus, observations are assumed to be independent across states, but not neces-
sarily within states over time. I establish time order by lagging the indepen-
dent variables one wave behind the dependent variable. I also include a
lagged-dependent variable as a predictor so that I am assessing the impact of
the independent variables on change in the Amnesty rating. I am sensitive to
potential collinearity in my models. Therefore, I report the OLS-based maxi-
mum variance inflation factor (VIF) score for each model. The maximum VIF
score across all models in Table 4 is always below 10, suggesting that collin-
earity is not a problem in these analyses.3
Sample
My base sample consists of 459 observations across 138 countries over
four waves during the 1980–2000 period. The pooled data are unbalanced
with some states contributing more observations than others. However, 114
states (83% of the total) are present across two or more waves, and 98 states
(71% of the total) are present in all four waves. Each wave represents a 6-
year period (1980–1985, 1985–1990, 1990–1995, and 1995–2000), where each
Ta
ble
4O
rder
edP
rob
itM
od
els
of
the
Am
nes
tyR
atin
g
(1)
(2)a
(3)b
(4)c
(5)d
(6)e
(7)f
(8)g
(9)h
New
spap
er
read
ersh
ip
.366**
(.105)
.375***
(.105)
.363**
(.106)
.374***
(.106)
.333**
(.106)
.354**
(.112)
.374**
(.112)
.444**
(.134)
.438**
(.147)
Am
nes
ty
rati
ng
(Lag
)
.555***
(.110)
.554***
(.110)
.553***
(.110)
.548***
(.110)
.600***
(.117)
.559***
(.131)
.412***
(.114)
.601***
(.146)
.186***
(.048)
Tim
eper
iod
.002
(.078)
.012
(.078)
.000
(.078)
).0
05
(.079)
.011
(.080)
.061
(.086)
.281**
(.093)
).0
86
(.158)
.056
(.046)
Lat
inA
mer
ica
).5
70***
(.132)
).5
27***
(.133)
).5
69***
(.132)
).5
73***
(.133)
).5
39***
(.136)
).5
62***
(.148)
).5
80***
(.128)
).6
20***
(.177)
).2
78***
(.073)
Afr
ica
).6
43**
(.193)
).6
01**
(.196)
).6
45**
(.194)
).6
48**
(.194)
).6
14**
(.207)
).5
25*
(.227)
).6
71***
(.188)
).8
41**
(.250)
).3
32**
(.097)
Mid
dle
Eas
t)
.643***
(.137)
).6
17***
(.136)
).6
42***
(.136)
).6
44***
(.136)
).6
26***
(.141)
).6
55***
(.153)
).6
16***
(.129)
).7
49**
(.224)
).3
59***
(.068)
Eas
tA
sia
).5
38***
(.124)
).5
15***
(.125)
).5
38***
(.125)
).5
39***
(.125)
).5
34***
(.129)
).5
83***
(.139)
).5
30***
(.121)
).6
72***
(.162)
).3
08***
(.065)
Eas
tern
Euro
pe
).3
75**
(.118)
).3
41**
(.117)
).3
74**
(.118)
).3
73**
(.118)
).3
07*
(.148)
).4
28*
(.171)
).4
00***
(.105)
).5
00**
(.144)
).1
92***
(.050)
Pre
ssfr
eedom
.041
(.119)
.022
(.121)
.041
(.119)
.040
(.119)
.019
(.124)
).0
45
(.130)
.063
(.117)
).1
10
(.137)
Dem
ocr
atiz
atio
n.1
21
(.104)
.133
(.104)
.123
(.104)
.124
(.104)
.108
(.107)
.188
(.122)
.107
(.101)
.275†
(.157)
.084†
(.049)
NEWSPAPER READERSHIP AND HUMAN RIGHTS 15
Ta
ble
4(C
on
tin
ued
)
(1)
(2)a
(3)b
(4)c
(5)d
(6)e
(7)f
(8)g
(9)h
rtia
ry
duca
tion
.121
(.121)
.045
(.125)
.123
(.121)
.090
(.127)
.176
(.127)
.175
(.138)
.201†
(.116)
.107
(.177)
.012
(.066)
DP
PC
PP
P)
.086
(.144)
.113
(.145)
.080
(.147)
.087
(.145)
.088
(.158)
.244
(.175)
.083
(.144)
).0
25
(.209)
vil
war
).3
43***
(.077)
).3
38***
(.077)
).3
43***
(.077)
).3
55***
(.078)
).3
43***
(.080)
).3
66***
(.089)
).3
27***
(.074)
).2
55**
(.094)
).1
96***
(.033)
pula
tion
ensi
ty
).0
96
(.084)
).0
63
(.088)
).0
94
(.085)
).0
96
(.085)
).0
81
(.088)
).0
96
(.093)
).0
39
(.084)
).1
25
(.112)
).0
34
(.042)
eaty
atifi
cati
ons
).0
27
(.086)
).0
36
(.087)
).0
29
(.086)
).0
14
(.089)
).0
33
(.087)
).0
76
(.093)
).1
01
(.092)
).1
71
(.119)
).0
49
(.047)
tern
atio
nal
rgan
izat
ions
).3
24**
(.119)
).3
13**
(.119)
).3
22**
(.119)
).3
19**
(.119)
).3
28*
(.131)
).4
21**
(.149)
).2
81*
(.110)
).3
79*
(.163)
).2
80***
(.080)
ade
pen
nes
s
.176*
(.071)
.172*
(.072)
.176*
(.071)
.184*
(.072)
.156*
(.074)
.116
(.080)
.129†
(.067)
.167†
(.100)
.127**
(.041)
Inew
s
elea
ses
).4
81***
(.078)
tern
etusa
ge
).0
83
(.106)
levis
ion
ouse
hold
s
.049
(.206)
ates
138
134
137
138
114
98
138
129
138
16 ROB CLARK
Te e
G
(
Ci
Po d
Tr r
In
o
Tr o
A
r
In Te h
St
Ta
ble
4(C
on
tin
ued
)
(1)
(2)a
(3)b
(4)c
(5)d
(6)e
(7)f
(8)g
(9)h
Obse
rvat
ions
459
443
457
458
435
392
459
224
459
Max
imum
var
iance
infl
atio
nfa
ctor
7.6
77.7
57.6
67.6
68.1
98.4
67.6
78.9
7R
2w
.048
i
Pse
udo
R-s
quar
e.1
87
.170
.186
.187
.190
.198
.203
.199
R2
b.7
17
j
BIC
2,5
99
2,5
80
2,5
95
2,5
95
2,4
87
2,2
16
2,5
62
1,2
58
R2
o.6
30
k
Note
s:E
ach
cell
report
sth
est
andar
diz
edco
effi
cien
tw
ith
the
robust
stan
dar
der
ror
inpar
enth
eses
.A
llm
odel
sin
clude
a
clust
ered
sandw
ich
esti
mat
or
toal
low
for
intr
a-st
ate
corr
elat
ion;
aE
xcl
udes
stat
esw
ith
per
fect
Am
nes
tyra
tings;
bE
xcl
udes
Am
nes
tyra
tings
bas
edon
the
US
SD
;cE
xcl
udes
outl
iers
;dE
xcl
udes
stat
esco
ntr
ibuti
ng
one
obse
rvat
ion;
eF
eatu
res
abal
ance
d
sam
ple
;f In
cludes
contr
ol
for
Am
nes
tynew
sre
leas
es;
gIn
cludes
contr
ols
for
Inte
rnet
usa
ge
and
tele
vis
ion
house
hold
s;hT
wo-
stag
ele
ast
squar
esre
gre
ssio
n,
wit
hpre
ssfr
eedom
and
GD
PP
Cse
rvin
gas
inst
rum
ents
for
new
spap
erre
ader
ship
;i R
2w
refe
rsto
R2
Wit
hin
;j R
2b
refe
rsto
R2
Bet
wee
n;
kR
2o
refe
rsto
R2
Over
all.
†p
<.1
0;
*p
<.0
5;
**p
<.0
1;
***
p<
.001
(tw
o-t
aile
dte
sts)
.
NEWSPAPER READERSHIP AND HUMAN RIGHTS 17
18 ROB CLARK
data point for each measure represents a state’s average value across the
entire wave (except where otherwise noted above). The four waves of the
dependent variable cover the 1985–2002 period (1985–1990, 1990–1995,
1995–2000, and 2000–2002), while the four waves of the lagged-dependent
variable cover the 1975–1995 period (1975–1980, 1980–1985, 1985–1990,
and 1990–1995).
Results
Regional Patterns and Longitudinal Trends
Table 3 reports newspaper readership trends and regional patterns for the
126 countries in my dataset that have circulation scores across all four waves.
In addition, I include trends for 23 Eastern European countries that report cir-
culation scores during the final two waves (see bottom row). The data reveal
considerable regional disparities that correspond broadly with socioeconomic
levels of development. In particular, Western nations feature readership rates
that are more than twice as large as any other region (254.80 during the
1995–2000 period). Latin America (81.48), the Middle East (90.83), East Asia
(107.47), and Eastern Europe (113.23) all have rates that are close to 100 by the
end of the sample period. By contrast, countries in Central and sub-Saharan
Africa (11.37) have circulation figures that are far lower than anywhere else in
the world.
In addition, Table 3 also reports longitudinal trends within each region
(see final column for overall rate of change). The first row reports the overall
trend. Readership increased slightly during the 1980s, before falling over the
last two time periods during the 1990s, contributing to an overall decline of
2.44 percent during the sample period. The 1990s decline roughly coincides
with the emergence of the Internet, particularly among advanced economies.
Accordingly, Western nations have driven the decline in newspaper circula-
tion. In this region, readership fell slightly during the 1980s, before falling
more rapidly during the 1990s, contributing to a regional decline in newspaper
circulation of 12.48 percent. By contrast, readership in Latin America
(5.69%), Africa (6.96%), and Eastern Europe (8.91%) show smaller declines.
Moreover, the Middle East (34.07%) and East Asia (12.48%) featured substan-
tial increases in newspaper circulation. Thus, while the decline of the news-
paper industry has been a salient theme in the West, this decline has not been
universal, at least during the sample period. Nevertheless, as a robustness
check, I test whether the effect of newspaper readership weakens or disappears
when controlling for Internet usage during the latter half of the sample period
(see Table 4, model 8).
NEWSPAPER READERSHIP AND HUMAN RIGHTS 19
Analyses
Table 4 presents results from the main analyses. In these models, I report
results from the ordered probit regression of the Amnesty International rating
on newspaper readership. Prior to analyses, I standardized all predictors
(mean = 0; standard deviation = 1) so that the reported coefficients allow
interested readers to compare the magnitude of each variable’s effect. Thus,
each cell reports the standardized coefficient with the robust standard error in
parentheses. Model 1 represents the base model, estimating the effect of news-
paper readership on a country’s Amnesty rating when controlling for the tech-
nical and substantive controls. The effect of newspaper readership is positive
and reaches statistical significance (p < .01). Thus, higher levels of newspaper
readership significantly improve a country’s human rights record when the
other variables are held constant. In fact, readership exerts the strongest effect
among all substantive predictors, displaying positive effects that are larger
(B = .366) than the negative effects of being in a civil war (B = ).343). The
model also reveals considerable regional disparities in human rights records,
as Western nations feature significantly higher human rights ratings than all
five non-Western regions.
In the remaining models featured in Table 4, I examine the effect of
newspaper readership under alternative specifications. In model 2, the sample
is restricted by excluding four states (16 observations) with perfect Amnesty
scores across all four waves of the sample period (Australia, Canada, the
Netherlands, and New Zealand). In model 3, the sample is restricted by drop-
ping two observations, Gabon (wave 4) and Norway (wave 4), based on the
U.S. State Department’s ratings of human rights. In model 4, the sample is
restricted by excluding one outlier (United States, wave 3) identified by the
Hadi procedure available in Stata 11.1. The procedure identifies multiple out-
liers in multivariate data using OLS (I use the p < .05 significance level for
my outlier cutoff). In model 5, I restrict the sample to those 114 states that
contribute two or more observations (N = 435). In model 6, the sample is bal-
anced, restricted to those 98 states present in all four waves of the sample per-
iod (N = 392). In each of these alternative specifications, newspaper
readership continues to positively affect a state’s Amnesty rating at a high
level of significance (p < .01 or greater).
In models 7–8, I estimate the impact of newspaper readership net of
additional controls. In model 7, I include a control that gauges the dispro-
portionate amount of attention that Amnesty International devotes to differ-
ent countries. One reason to include this control is that Amnesty’s human
rights ratings may be influenced by the amount of attention that it devotes
to each country. Thus, it may be interesting to examine the effect of
20 ROB CLARK
newspaper readership net of this possibility. Second, the control could also
be mediating the effect of newspaper readership. Previous studies have
examined factors that increase the support of human rights issues (Carpenter
2007) and domestic social movements (Bob 2001) by transnational advocacy
networks, including groups such as Amnesty International and other non-
governmental organizations. In particular, Keck and Sikkink (1998) describe
a ‘‘boomerang pattern,’’ in which local actors bypass the state and seek
allies in global civil society who will, in turn, pressure states from the out-
side. Accordingly, one possible explanation for the positive effect of news-
paper readership is that the print media may influence external actors by
providing them with information regarding domestic human rights practices.
This, in turn, may lead international advocacy groups to apply greater pres-
sure on the state. Thus, in model 7, I consider Amnesty International’s
‘‘advocacy effort’’ by controlling for the number of press releases it issues
per country during each wave of the sample period. Data come from
Amnesty International’s Country Dossiers and Publications, 1962–2009(Amnesty International 2011). The results show that controlling for
Amnesty’s news release activity does not substantially influence the positive
effect of newspapers (p < .01).
In model 8, I consider alternative forms of media consumption during the
1990s by controlling for each country’s Internet usage and television market.
Internet usage is defined as the number of people (per 100 in the population)
with access to the worldwide network. I also include a control for television
saturation, measured as the percentage of households with television sets. Data
for these measures come from the World Development Indicators (Interna-
tional Bank for Reconstruction and Development 2007, 2010) and are avail-
able during the latter half of the sample period, 1990–2000, which coincides
with the emergence of the electronic news media and the decline of the news-
paper industry among developed nations. Including these controls reduces my
sample to 224 observations across 129 states during the final two waves of the
sample period. Newspaper readership is correlated with both Internet usage
(r = .571) and television households (r = .598). However, as the maximum
VIF score indicates (8.97), collinearity is not problematic. More importantly,
as the results from model 8 show, newspaper readership remains highly signif-
icant as a positive predictor (p < .01).
Finally, it is possible that the relationship between newspaper readership
and human rights suffers from endogeneity (i.e., reverse causality). For exam-
ple, repressive human rights practices may compel governments to shut down
or hinder press activity, while reformed governments may encourage greater
press activity. Thus, in model 9, I corrected for potential endogeneity via
instrumental variables regression using two-stage least squares (2SLS)
NEWSPAPER READERSHIP AND HUMAN RIGHTS 21
estimation for panel-data models. Diagnostics reveal that the instruments
(press freedom and GDP PC) are both strong (i.e., correlated with newspaper
readership) and valid (i.e., uncorrelated with the error term). Moreover, the
results shown in model 9 reveal that newspaper readership remains a signifi-
cant, positive predictor of human rights (p < .01).
Discussion
Previous research has found that the print media can effectively educate
citizens, shape their attitudes, and mobilize them to become politically active.
In this study, I examine the print media’s impact on human rights in a cross-
national context. The findings from this study reveal that a nation’s level of
newspaper readership positively affects change in its Amnesty International
rating, net of a broad set of controls. This relationship is robust to a number
of alternative specifications, including models that consider the impact of
ceiling effects, measurement bias, influential observations, sample composi-
tion, mediation, and endogeneity. Moreover, the magnitude of the print
media’s impact is substantial, exerting large effects relative to other substan-
tive predictors and rivaling the negative impact of being in a civil war. In
addition, I do not find that the effect of newspaper readership on human rights
significantly declines in the latter half of the sample period or that the impact
of the newspaper industry was weakened by the emergence of alternative
media, such as the Internet or television.
The positive effect of newspaper readership on human rights during the
final years of the twentieth century coincides with an era that features substan-
tial critique and scrutiny directed toward the news media. The media have
been accused of bending to crass commercialism, political bias, and govern-
ment influence across a number of countries. Within this context, it is unclear
what impact (if any) the recent trend of liberalization has had on media sys-
tems. In most parts of the world, the news media have become more market-
oriented since the 1980s because of privatization and deregulation (Curran
et al. 2009). However, this has not always resulted in greater press freedom, a
more educated citizenry, or more transparent governments. Rather, the privati-
zation of media has led scholars to draw a variety of conclusions across differ-
ent countries around the world. By one account, the commercialization of
India’s television industry has provided viewers with independent media alter-
natives to state-monitored media outlets and has provided its TV journalists
with new opportunities for voicing the concerns of marginalized populations
and demanding government accountability (Rao 2008). Similarly, as a result
of Mali’s democratic transition and media liberalization during the 1990s, it
now has the greatest amount of press freedom in West Africa (Nisbet 2008).
Conversely, other research points to shortcomings in privatized media systems.
22 ROB CLARK
For example, one study comparing several Western countries finds that media
systems operating under a public service model (i.e., Finland and Denmark)
produce more knowledgeable citizens than media systems representing a pure
market model (i.e., the United States) (Curran et al. 2009). In sum, the privati-
zation of media outlets has led scholars to draw different conclusions across
different national contexts.
In addition to liberalization, the newspaper industry has had to face its
own mortality, weathering significant declines in circulation in some parts of
the world beginning in the early 1990s, which has also caused many to ques-
tion its relevance. Against this backdrop, the present study addresses an impor-
tant set of issues in media research. Can the media be rightfully construed as
public service representatives, capable of monitoring the state, while educating
and mobilizing citizens? The findings from this study answer in the affirmative
and suggest that newspapers continued to serve an important public function
during the sample period. Rather than viewing the newspaper industry as a
declining worldwide institution, it is more accurate to suggest that declines in
readership are region-specific, as many nations in the developing world (e.g.,
those in the Middle East and East Asia) experienced significant circulation
increases during the sample period. Moreover, there is evidence that newspa-
per circulation has continued to rise (or has remained stable) in most parts of
the world during the post-2000 period. Over the past 5 years, newspaper sales
worldwide increased by 9.39 percent, with circulation rates rising or remaining
stable in 75 percent of the world during this time (World Association of
Newspapers 2008). Moreover, despite the continued circulation declines in
Western countries, many of these countries have begun to distribute ‘‘free dai-
lies,’’ which now account for 23 percent of all newspaper circulation in
Europe. In fact, 70 percent of the world’s free dailies are distributed in Europe
(Bakker 2007). Between 1995 and 2007, the worldwide circulation of free dai-
lies has grown from 200,000 to over 40 million (Bakker 2007). And, over the
past 5 years, the global circulation of free dailies has increased by 173.2 per-
cent, such that they now account for 7 percent of circulation around the world
(World Association of Newspapers 2008).
Nevertheless, even with the injection of free dailies, persistent declines in
circulation in some countries during the post-2000 era suggest that the indus-
try may have to fulfill its public service role in an electronic format. To that
end, online newspaper sites around the world have grown by over 50 percent
during the past 5 years (World Association of Newspapers 2008). Future
research should investigate more closely whether newspapers will be able to
make the Internet transition and continue to monitor state activity in the same
capacity. In this study, I report the effects of newspaper readership during the
post-1990 period when controlling for a country’s Internet usage (see Table 4,
NEWSPAPER READERSHIP AND HUMAN RIGHTS 23
model 8). While this measure has limitations, Internet usage does provide us
with a preliminary glimpse of the impact that this form of media may have on
human rights practices. As the above model indicates, the effect of Internet
usage is non-significant. To the extent that these results reflect true differences
between newspapers and the Internet, one can speculate that the experience of
online news consumption may mimic that of television viewing more so
than that of newspaper reading. However, future work that examines more pre-
cise measures of online news consumption are required before definitive
conclusions can be drawn.
ENDNOTES
*I thank Amy Kroska for her generous assistance. I am also grateful to Emilie Hafner-Bur-
ton and Jenifer Whitten-Woodring for kindly sharing their data. Please direct correspondence to:
Rob Clark, Department of Sociology, University of Oklahoma, Kaufman Hall 331, 780 Van Vleet
Oval, Norman, OK 73019, USA; e-mail: [email protected] come from the World Development Indicators (International Bank for Reconstruction
and Development 2004), unless otherwise noted.2In my base sample of 138 states, 37 are coded as having press freedom throughout the sam-
ple period: Australia, Austria, Belgium, Botswana, Canada, Colombia, Costa Rica, Croatia,
Cyprus, Czech Republic, Denmark, Dominican Republic, Ecuador, Finland, France, Gambia,
Germany, India, Ireland, Israel, Italy, Jamaica, Japan, Latvia, Mauritius, Mexico, Nepal, Nether-
lands, New Zealand, Norway, Spain, Sweden, Switzerland, Trinidad-Tobago, Uganda, United
Kingdom, and United States.3In separate analyses, I also estimated a fixed-effects model that restricts attention to longitu-
dinal variation (thereby ignoring all cross-sectional differences). The results are similar to those
presented below, with newspaper readership (b = .363; p < .05) exerting a positive, significant
effect on the Amnesty rating.
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