# Far-right movements in the Western world: How media exposure relates to normative beliefs and attitudes toward the far-right

Hema Preya Selvanathan, Bernhard Leidner, Stylianos Syropoulos, Winnifred Louis, Levi Adelman, Aphrodite Baka, Christina Bauer, Martijn Blikmans, Maja Becker, Eszter Beran, et al.

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## To cite this version:

Hema Preya Selvanathan, Bernhard Leidner, Stylianos Syropoulos, Winnifred Louis, Levi Adelman, et al. Far-right movements in the Western world: How media exposure relates to normative beliefs and attitudes toward the far-right. Group Processes and Intergroup Relations, 2025, 10.1177/13684302241309554. hal-04959065

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Article

Far-right movements in the Western
world: How media exposure relates
to normative beliefs and attitudes
toward the far-right

Group Processes & Intergroup Relations

1-21

© The Author(s) 2025

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DOI: 10.1177/13684302241309554

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Sage

Hema Preya Selvanathan,¹ ID Bernhard Leidner,² ID

Stylianos Syropoulos,³ ID Winnifred Louis,¹ Levi Adelman,⁴ ID

Aphrodite Baka,⁵ Christina Bauer,⁶ Martijn Blikmans,⁷ Maja Becker,⁸ ID

Eszter Beran ID, ⁹ Michał Bilewicz,¹⁰ ID Peggy Chekroun,¹¹

Tobias Greitemeyer,¹² ID Bettina Hannover,¹³ ID Inga Jasinskaja-Lahti,¹⁴ ID

Peter Kardos ID,¹⁵ Mengyao Li,¹⁶,¹⁷ Torun Lindholm,¹⁸ Steve Loughnan,¹⁹ ID

Theresa Mros,¹³ Maria Paola Paladino,²⁰ Marina Papadopoulou,⁵

Daniel R. Rovenpor,²¹ Kathrin Sadus,²² Jeroen Vaes,²⁰ ID Alain Van Hiel²³

and Martijn van Zomeren⁷ ID

Abstract

Considering the rise of far-right groups in Western countries, we examined whether exposure to media coverage on the far-right is associated with attitudes toward it, using surveys in 15 Western democratic countries (total N = 2,576). We hypothesized that greater media exposure to the far-right will be associated with greater perceived prevalence and acceptability of it, which will in turn be associated with divergent attitudes. On the one hand, greater perceived prevalence may be associated with more unfavorable attitudes toward the far-right (a threat response). On the other hand, greater perceived acceptability may be associated with more favorable attitudes toward the far-right (a normalization response). Overall, there was more evidence for a threat response than a normalization response: media exposure was consistently related to greater perceived prevalence (but not acceptability) of the far-right. This research underscores the importance of studying the consequences of the rise of the far-right.

Keywords

far-right, media effects, normalization, polarization, social movements, social norms

Paper received 6 February 2024; revised version accepted 11 November 2024.
In societies across the Western world, far-right mobilization continues to take hold (Norris & Inglehart, 2019; Pahnke, 2021). In Italy, for example, CasaPound is a fascist, extreme neo-Nazi group that has made headlines over the last decade for its confrontational street demonstrations and the occupation of public buildings (Gattinara & Froio, 2014). In Germany, the Alternative for Germany (AfD) is a radical, far-right, populist political party that has won seats in federal elections in 2017 and 2021 (Hansen & Olsen, 2022; Lees, 2018). Such far-right groups that were previously part of the periphery have now been increasingly featured in mainstream public discourse and have therefore grown to become influential actors in the sociopolitical sphere (Brown & Mondon, 2021; Gattinara & Froio, 2019). As far-right groups continue to mobilize in public spaces, they are also increasingly portrayed in mainstream media. However, relatively little is known about the consequences of media coverage of far-right movements for public opinion towards such movements.

While far-right movements are diverse in their goals and philosophies, they are typically rooted

in a nativist and nationalist ideology that seeks to protect and defend the traditional values of a dominant group that are perceived to be under threat from other groups within society (Mudde, 2007; Rydgren, 2007). The far-right encompasses both the extreme and radical right; the extreme right rejects democracy and tends to resort to violence, whereas the radical right draws on populist ideals to oppose liberal ideologies (Mudde, 2007). The repertoires of the far-right range from grassroots activism and direct action to party politics and electoral campaigns—all of which aim to mobilize broader public support. As such, the rise of the far-right can be understood as a social movement (Gattinara & Pirro, 2019; Simi et al., 2024).

A key question is whether the broader public's exposure to media coverage of the far-right has implications for societal beliefs and attitudes toward these groups. Are far-right groups viewed as becoming increasingly prevalent in society, and if so, does that promote public concern about the potentially negative effects of the far-right on society? Or, are far-right groups viewed as

<footnote n="1">¹The University of Queensland, Australia</footnote>

<footnote n="2">²University of Massachusetts Amherst, USA</footnote>

<footnote n="3">³College of Global Futures, Arizona State University, USA</footnote>

<footnote n="4">⁴Utrecht University, the Netherlands</footnote>

<footnote n="5">⁵Aristotle University of Thessaloniki, Greece</footnote>

<footnote n="6">⁶University of Vienna, Austria</footnote>

<footnote n="7">⁷University of Groningen, the Netherlands</footnote>

<footnote n="8">⁸CLLE, Université de Toulouse, CNRS, France</footnote>

<footnote n="9">⁹Pázmány Péter Catholic University, Faculty of Humanities and Social Sciences, Hungary</footnote>

<footnote n="10">¹⁰University of Warsaw, Poland</footnote>

<footnote n="11">¹¹Université Paris Nanterre, France</footnote>

<footnote n="12">¹²University of Innsbruck, Austria</footnote>

<footnote n="13">¹³Freie Universität Berlin, Germany</footnote>

<footnote n="14">¹⁴University of Helsinki, Finland</footnote>

<footnote n="15">¹⁵Kean University, USA</footnote>

<footnote n="16">¹⁶Max Planck Institute for Research on Collective Goods, Germany</footnote>

<footnote n="17">¹⁷Queen's University Belfast, Northern Ireland</footnote>

<footnote n="18">¹⁸Stockholm University, Sweden</footnote>

<footnote n="19">¹⁹University of Edinburgh, Scotland</footnote>

<footnote n="20">²⁰University of Trento, Italy</footnote>

<footnote n="21">²¹Baruch College, USA</footnote>

<footnote n="22">²²Heidelberg University, Germany</footnote>

<footnote n="23">²³Ghent University, Belgium</footnote>

<footnote>**Corresponding author:**</footnote>

<footnote>Hema Preya Selvanathan, School of Psychology, The University of Queensland, St Lucia, Queensland 4072, Australia.</footnote>

<footnote>Email: h selvanathan@uq.edu.au</footnote>
becoming increasingly accepted in society, and if so, do people come to tolerate these groups' ideology and their right to mobilize? In the present research, we investigated for the first time whether and how exposure to media coverage of far-right groups could potentially be related to divergent perceptions of social norms about these movements, and, subsequently, how these perceived norms relate to personal attitudes toward the far-right. We address these questions through cross-national surveys conducted in 15 Western countries that have witnessed the rise of the far-right. Specifically, we focused on people who were not ideologically aligned with the far-right and may therefore constitute a potential audience targeted by far-right mobilization efforts.

## *The Role of the Media in Shaping Social Norms*

One of the ways that people come to understand and construct social norms about various ongoing social and political issues is through the media. Media exposure can make certain issues or perspectives more dominant in the public sphere (McCombs, 2002). Scholars have long noted that the media serves an agenda-setting function whereby the topics and issues covered by the media increase their salience and subsequently influence public opinion (for a review, see Bryant & Oliver, 2009). There is extensive evidence that the media plays a role in shaping sociopolitical attitudes. In the context of immigration in Europe for example, mass coverage about immigration was correlated with anti-immigrant policy attitudes and socially conservative voting preferences (Eberl et al., 2018). The heightened visibility of immigration in the news can exert an influence on anti-immigrant attitudes regardless of the actual rates of immigration (Van Klingeren et al., 2015). This research is largely based on linking fluctuations of news coverage on various topics with panel surveys of relevant public attitudes over time. Relatedly, studies have investigated self-reported media consumption and attitudes toward minorities, showing for example that

greater consumption of mass media that includes representation of gender and sexual minorities is associated with more positive attitudes towards lesbian, gay, bisexual, and transgender (LGBT) individuals (Calzo & Ward, 2009; Yan, 2019).

Although these studies largely did not explicitly examine the role of the media in social norms per se, it has been theorized that the mechanism through which the media shapes attitudes is by influencing perceived norms, that is, people's understandings of the informal rules that guide one's beliefs, attitudes, and behaviors within a society (Lapinski & Rimal, 2005). In Italy, it was found that exposure to right-wing media was related to weaker beliefs in the existence of a social norm that condemns discrimination, which in turn predicted greater prejudice towards immigrants (Vaes et al., 2015). Given the role of the media in shaping social norms, norm-based interventions have often used media campaigns to promote desirable behaviors in society (for reviews, see Cialdini & Goldstein, 2004; Tankard & Paluck, 2016; Wakefield et al., 2010). People's subjective perceptions of what is considered normative are highly malleable—and these perceptions tend to guide their own attitudes. As such, social norms, as derived from one's environment including the media, constitute an important vehicle for social influence. The present research will extend this work to the context of exposure to far-right mobilization in the media.

This focus is important because far-right movements are increasingly featured in mass media, and they also have actively mobilized online by posting content on social media, blogs, and online news sites (Gallaher, 2020; Mondon & Winter, 2020). Big data analysis has shown an increased prevalence of terms focused on political extremism in media outlets between 1970 and 2019 both in the UK and the US; this is particularly pronounced for terms denoting right-wing political extremism (Rozado & Kaufmann, 2022). Research by media and communication scholars has further shown that media coverage of radical far-right groups often employs discursive strategies that accommodate their views, effectively providing them with a platform to disseminate
racist, exclusionary rhetoric as a legitimate politi-
cal stance (de Jonge & Gaufman, 2022; see also
Ekström et al., 2020). This phenomenon under-
scores the media’s crucial role in shifting societal
norms in terms of what is considered common-
place and normal in public discourse. Increased
media coverage of the far-right can have far-
reaching implications, including affecting the
treatment of minority groups, eroding social
cohesion, and posing challenges to the founda-
tions of democracy (Mondon & Winter, 2020;
Norris & Inglehart, 2019).

We propose two processes for how the media
might affect perceived social norms regarding
far-right groups. First, by increasing the salience
of an issue, exposure to media coverage of far-
right groups could promote the perceived preva-
lence of these groups. People may come to
believe that far-right groups are increasingly pop-
ular and have been gaining more supporters, sim-
ply because of their regular portrayal in the news.
Drawing on the social norms literature, such per-
ceptions can be conceptualized as *descriptive norms*,
that is, the perceived prevalence of a behavior in
society, or behaviors that are believed to com-
monly occur (i.e., what others typically do;
Cialdini et al., 1990; Kallgren et al., 2000).

Indeed, related evidence suggests that media
exposure can lead people to perceive certain
behaviors as more typical in society. For example,
news exposure has been linked to fear about
crimes independent of actual crime rates (Romer
et al., 2003), and consumption of news that depict
immigrants negatively leads people to overesti-
mate the frequency of immigrants as criminal
offenders (Arendt, 2010). Similarly, as the news
may sensationalize coverage of terrorism, the
consumption of news media can heighten the
perceived risk of terrorism (Nellis & Savage,
2012). By extension, by virtue of seeing mass cov-
erage of far-right groups, people may come to
think about these groups as becoming increasingly
widespread in society and view their activities as
quite common, regardless of the actual situation.
We propose that greater exposure to media cover-
age of the far-right will be linked to greater per-
ceived prevalence of this type of groups (i.e.,
strong descriptive norms).

Second, exposure to news coverage of the far-
right may increase the sense of how tolerated or
appropriate these groups are within society.
Simply being featured in mainstream outlets
could contribute to the perception that the activi-
ties of the far-right are not so fringe as they per-
haps once were; as such, the far-right may come
to be viewed as increasingly acceptable by the
public. Indeed, scholars have argued that the
media has been mainstreaming far-right groups
by providing coverage of their activities and
agenda (de Jonge & Gaufman, 2022; Ekström et
al., 2020). Regardless of the tone or framing of
the coverage, media content about the far-right
provides the group with a platform to share their
views with the broader society. As this happens
more frequently, it could create a perception that
far-right groups are not so radical after all, but
rather, they are a normal and acceptable part of
the political sphere. Drawing on the social norms
literature, we propose that such perceptions can
be conceptualized as *injunctive norms*, which com-
prise the perception of acceptable or approved
standards of behavior in society (i.e., what others
should do; Cialdini et al., 1990; Kallgren et al.,
2000).

As with any social movement, media portrayal
is key to raising awareness and ultimately galva-
nizing support from the public (Baugut &
Neumann, 2019; Walgrave & Vliegenthart,
2012). In the same way, a far-right movement’s
appeal, and ability to disseminate their message,
is partially dependent upon gaining widespread
news coverage (Ellinas, 2010). Since the media
holds agenda-setting power, media attention on
issues that are central to the far-right, such as
immigration or crime, can condone and vindic-
cate their policy agenda (Boomgaarden &
Vliegenthart, 2007; Walgrave & De Swert, 2004).
As such, the far-right may come across as a legiti-
mate political group that should be tolerated and
respected. Specifically, we propose that greater
exposure to media coverage of the far-right will
be linked to greater perceived acceptability of
this ideology (i.e., strong injunctive norms). By
extension, we propose that these perceptions of
the social norms around the far-right (i.e.,
descriptive and injunctive norms) as a result of
media exposure will be linked to differing attitudes toward the far-right.

## Threat and Normalization Responses to the Far-Right

We propose that perceived norms around the far-right as a result of media exposure can result in a dual process: a threat response and a normalization response. First, why might people show a threat response? The influence of social norms on attitudes and behaviors is well established in various literatures (e.g., Lapinski & Rimal, 2005; Tankard & Paluck, 2016). People tend to internalize and comply with the descriptive norms within their ingroup—that is, the groups with which people are strongly identified (Cialdini et al., 1990; Hogg et al., 1990; Smith & Terry, 2003)—while rejecting outgroup norms (Turner & Reynolds, 2012). In the case of the far-right, members of the broader society are likely to view this movement as a vilified outgroup. They are typically viewed as ideologically opposed to broader mainstream values within a country, and, as a result, tend to be stigmatized or portrayed as political outcasts (e.g., Mendes & Dennison, 2021; Van Spanje & Van Der Brug, 2007). It has further been found that groups that are viewed as threats to the dominant culture and worldview are believed to be more pervasive in the community, in the sense that people tend to overestimate the presence of the group (Ponce de Leon et al., 2022).

Past research has also shown that, at times, people may be motivated to resist a social norm (Hornsey et al., 2003). When people believe that their ideological position is losing ground within society, they are more likely to want to speak out and resist the change (Louis et al., 2010). Further, people experience collective anger, guilt, and shame in response to the actions of their country that they are ideologically opposed to (e.g., the U.S. occupation of Iraq), which promotes political protest (Iyer et al., 2007). What this literature suggests is that people are likely to demonstrate a threat response by opposing and mobilizing against societal norms that are not in line with the

norms of their ingroup. Thus, we hypothesized that viewing the far-right as becoming increasingly prevalent in society (high descriptive norms) will be linked to more negative attitudes toward this movement, constituting a threat response.

Second, why might people show a normalization response? Injunctive norms tend to shape people's attitudes and behaviors in line with the norm because it is an indicator of what is expected and acceptable in a society (Cialdini et al., 1990). Perceived injunctive norms are related to what people personally value. Within the domain of prejudice for example, the perceived normative acceptability of prejudice towards various groups corresponds strongly with people's own prejudice levels towards these groups (Crandall et al., 2002), and being exposed to non-prejudiced individuals tend to promote nonprejudiced behaviors and attitudes in others (Masser & Phillips, 2003). What this suggests is that people's personally held attitudes are bound up with their perceptions of what others find acceptable. Perceptions of injunctive norms have also been found to shape what people think is normal (Rettie et al., 2013).

Within the context of fringe groups such as the far-right, the literature suggests that when they are viewed as becoming more accepted in society, people tend to change their publicly espoused views to be in line with the perceived social norms. For example, people were far less likely to publicly oppose a far-right political party in the 2012 French presidential election when they thought others in their surroundings voted in support of that party (Portelinha & Elcheroth, 2016). There is also a demonstrated effect of desensitization that is related to the phenomenon of normalization. Essentially, repeated exposure to hateful speech towards a group can make such sentiments appear commonplace and acceptable (Soral et al., 2020). This sets a dangerous precedent as people's tolerance for derogatory speech increases with greater exposure to such speech (Bilewicz & Soral, 2020; Soral et al., 2018). In fact, it has been found that when Americans perceive the Alt-Right movement in the US as gaining acceptance in society, they are more likely to
personally accept and tolerate far-right views, regardless of their own political allegiance (Selvanathan & Leidner, 2022). Consequently, we propose that perceiving the far-right as becoming increasingly acceptable in society (i.e., high injunctive norm) will be associated with more favorable attitudes toward that movement. This constitutes a normalization response.

## Present Research

We hypothesized that exposure to media coverage of the far-right will be associated with normative beliefs about the far right, both in terms of greater perceived prevalence (i.e., high descriptive norms) and greater perceived acceptability (i.e., high injunctive norms). In line with prior research, we further hypothesized that these normative beliefs would have differential associations with personally held attitudes toward the far-right (Selvanathan & Leidner, 2022). Specifically, on the one hand, greater perceived prevalence of the far-right is expected to be associated with less favorable attitudes toward it, thereby constituting a threat response. On the other hand, greater perceived acceptability of the far-right is expected to be associated with more favorable attitudes toward it, thereby constituting a normalization response. For a conceptual model of the hypothesized effects, see Figure 1.

We examined these questions in 15 Western democracies focusing on different far-right movements within those countries (see Table 1 for details). The present research is a crucial extension of our past research that has shown experimental evidence for the effect of perceived acceptability (but not prevalence) of the Alt-Right (a far-right, White nationalist movement in the US) on more positive public attitudes towards the movement (Selvanathan & Leidner, 2022). The present research examined the role of media exposure as a precursor to perceived social norms and public attitudes towards far-right movements. We also examined for the first time whether the hypothesized mechanisms (i.e., a threat and a normalization response) emerge across a range of countries with different sociopolitical contexts that have witnessed the rise of the far-right.

It is important to note that our conceptualization of public attitudes toward the far-right was not about directly joining the group, which we expected would be low at the societal level. There may be social desirability concerns because explicitly supporting far-right groups may be a taboo (Terman, 2020). As such, we instead captured related beliefs and appraisals that would imply indirect support for (or opposition towards) the far-right, and potentially more insidious and hidden effects. Anti-far-right attitudes relate to concerns over the negative effects of the far-right, including perceived harm of their speech (Cowan et al., 2002), negative emotional responses to the movement (Leets, 2001), perceived threat from it (Riek et al., 2006), and support for pro-minority policies (Iyer et al., 2007). Together, we took these perceptions to imply unfavorable attitudes towards the far-right.

By contrast, pro-far-right attitudes were about supporting the rights and ideas of the far-right. Pro-far-right attitudes encompass believing that the far-right's speech (including explicitly racist speech) should be protected as free speech (Roussos & Dovidio, 2019; White & Crandall, 2017), having tolerance for far-right mobilization activities (Nelson et al., 1997), and perceiving bias against the dominant group within society (Wilkins & Kaiser, 2014), which reflects the sentiment of victimization espoused by far-right groups (Forscher & Kteily, 2020). These perceptions would together imply that people are showing some degree of sympathy towards the far-right, albeit indirectly. Taken together, our outcome variables of attitudes toward the far-right (i.e., pro- and anti-far-right attitudes) relate to the extent to which people show leniency to them versus how much they are alarmed by the rise of this movement.

## Method

### Participants

We recruited samples from 15 countries: Australia, Austria, Belgium, England, Finland, France, Germany (led by researchers based in Berlin and Heidelberg), Greece, Hungary, Italy,
<figure><img src="image_5.png" /><figcaption>**Figure 1.** Conceptual model of the hypothesized effects.</figcaption></figure>

the Netherlands, Poland, Scotland, Sweden, and the US. Two samples from Germany were recruited to ensure sufficient response rates: one from a research team located in Berlin and one from a research team located in Heidelberg; however, the participants were recruited from all over the country and were combined into a single sample.¹ In each country, participants were recruited from colleges/universities. It is worth noting that this sampling strategy means that our participants are likely to be quite different from the general population (Hanel & Vione, 2016), thereby limiting the generalizability of findings. However, it was not possible for us to recruit community samples or more representative ones due to funding constraints and lack of feasibility in some regions. To ensure our samples were somewhat comparable across the different national contexts, we recruited undergraduate students in each country so that the samples were at least similar in terms of key demographic background such as age, education level, and political leaning (i.e., young adults who are pursuing a college education and who tend to be politically left-wing; see Table 1 for participants’ demographic information per country).

Our exclusion criteria were as follows: (a) not being a citizen of the specific country, (b) not racially identifying with the majority racial group within the country (because some far-right groups endorse racial ethno-nationalist ideologies that

target racial minorities), (c) being a member of the target right-wing group, and (d) not being a student. After applying these exclusion criteria in each country, a total of 2,576 undergraduate students remained in our final sample. In this sample, 1,992 students were female, 563 were male, and 21 were nonbinary or indicated another gender identity. Participants’ age ranged between 17 and 64 years (M = 21.39, SD = 4.68). In terms of political orientation, the sample was generally left-leaning (M = 3.75, SD = 1.86) on a 9-point scale (1 = *very left-wing*, 9 = *very right-wing*).

## Procedure

The surveys were fielded online in 2019. In countries where English is the official language (i.e., Australia, England, Scotland, and the US), the questionnaire was administered in English. In all other countries, the questionnaire was translated into the official language of the country and then back-translated by the local research team to ensure that it was compatible across languages. There was at least one member of the research team that lived and worked in each of the 15 countries we studied. This approach ensured that the survey in each country was appropriately adapted to the local cultural and political context. To select the specific far-right movement in each country, local collaborators were consulted to ensure that the far-right groups selected were
<table><caption>**Table 1.** Information on far-right groups by country.</caption><thead><tr><th></th><th>Country</th><th>Far-right group</th><th>Details</th></tr></thead><tbody><tr><td>1</td><td>Australia</td><td>One Nation</td><td>Right-wing populist party</td></tr><tr><td>2</td><td>Austria</td><td>Freedom Party of Austria</td><td>Right-wing populist and national-conservative party</td></tr><tr><td>3</td><td>Belgium</td><td>Vlaams Belang</td><td>Right-wing populist and Flemish nationalist party</td></tr><tr><td>4</td><td>England</td><td>Britain First</td><td>Far-right, fascist party</td></tr><tr><td>5</td><td>Finland</td><td>Finns Party</td><td>Right-wing populist party</td></tr><tr><td>6</td><td>France</td><td>The National Rally</td><td>Right-wing populist and nationalist party</td></tr><tr><td>7</td><td>Germany</td><td>Alternative for Germany</td><td>Right-wing populist party</td></tr><tr><td>8</td><td>Greece</td><td>Golden Dawn</td><td>Utranationalist far-right party</td></tr><tr><td>9</td><td>Hungary</td><td>Our Homeland Movement</td><td>Far-right party</td></tr><tr><td>10</td><td>Italy</td><td>CasaPound</td><td>Far-right neo-fascist movement and former political party</td></tr><tr><td>11</td><td>The Netherlands</td><td>Party for Freedom</td><td>Right-wing populist and nationalist party</td></tr><tr><td>12</td><td>Poland</td><td>National Radical Camp</td><td>Right-wing, fascist, and ultranationalist party</td></tr><tr><td>13</td><td>Scotland</td><td>UK Independence Party</td><td>Right-wing populist and Eurosceptic party</td></tr><tr><td>14</td><td>Sweden</td><td>Swedish Democrats</td><td>Right-wing populist and nationalist party</td></tr><tr><td>15</td><td>USA</td><td>Alt-Right</td><td>Far-right White nationalist movement</td></tr></tbody></table>

somewhat comparable and grounded in similar ideologies, especially in terms of holding ethno-nationalist values, xenophobic beliefs, and endorsing right-wing populism. Furthermore, the far-right groups we selected have been described as radical-right groups in the media (e.g., see “Europe and right-wing nationalism: A country-by-country guide” 2019) and have been classified as far-right groups by scholars who have conducted comparative research of these groups (e.g., Davis & Deole, 2017; Golder, 2016; Lubbers & Coenders, 2017; Lubbers et al., 2002; Mudd, 2016; Rydgren, 2018).

All measures except media exposure were identical to a recent investigation conducted by members of the research team (Selvanathan & Leidner, 2022). Scale reliabilities for each country and measurement invariance tests are reported in the Supplemental Material. The study was preregistered (see https://aspredicted.org/PCV_TBN), and we note any deviations from the preregistration. Data and study materials are available on the Open Science Framework (OSF): https://osf.io/n8esu/.

**Media exposure.** Seven face-valid items were developed to assess media exposure to the far-right: (1) “In general, over the past month, how often

would you say you have seen or heard news coverage on [far-right group of each country]?”; (2–7) “Over the past month, how often have you come across news about [far-right group of each country] in each of the following news media?” (a) print news media, (b) online news articles, (c) online blogs or commentaries, (d) television or cable news, (e) radio stations, (f) social media. All responses were anchored on a 9-point scale (1 = *not at all*, 9 = *frequently*).

**Perceived prevalence.** Five items measured perceived prevalence of the far-right (descriptive norms) by asking participants about their opinion on the current situation in their country regarding the presence of this movement. An example question is, “The [far-right group] in [country] is. . .,” with various labels for the scale anchors (e.g., 1 = *not prevalent at all*, 9 = *very prevalent*; 1 = *not common at all*, 9 = *very common*).

**Perceived acceptability.** Five items measured perceived acceptability of the far-right (injunctive norms) by asking participants to indicate their perceptions of how other citizens in their country feel about the far-right. An example question stem was, “I believe that most [country citizens] find [far-right group]. . .,” with various labels for
the scale anchors (e.g., 1 = *unacceptable*, 9 = *acceptable*, 1 = *intolerable*, 9 = *tolerable*).

## Public attitudes toward the far-right

**Pro-far-right reactions.** We computed the average of three aspects that capture pro-far-right attitudes: (a) support for the protection of far-right speech under the consideration of free speech (six items adapted from Cowan et al., 2002; e.g., “I think that the ideas and beliefs [far-right group] has expressed in public are about free exchange of ideas, and must be allowed in a free society”; 1 = *strongly disagree*, 9 = *strongly agree*); (b) support for the notion that the far-right should be allowed to promote their ideas in the general public (three items adapted from Skitka et al., 2004; e.g., “In your opinion, should [far-right group] be allowed to have a public forum to give speeches?”; 1 = *no, absolutely not*, 9 = *yes, absolutely*); (c) perceived bias against the dominant racial/ethnic group (four items adapted from Wilkins & Kaiser, 2014; e.g., “Prejudice and discrimination against White people are on the rise”; 1 = *strongly disagree*, 9 = *strongly agree*).

**Anti-far-right reactions.** We computed the average of four aspects that capture anti-far-right attitudes: (a) perceptions of far-right speech as harmful (six items adapted from Cowan et al., 2002; e.g., “I think that the ideas and beliefs [far-right group] has expressed in public can violate the civil rights of groups that are targeted by it”; 1 = *strongly disagree*, 9 = *strongly agree*); (b) negative emotional reactions when thinking about the far-right (nine items; e.g., “When thinking about [far-right group] in [country], to what extent do you feel worried?”; 1 = *not at all*, 9 = *extremely*); (c) perceived threat from the far-right (five items adapted from Brambilla et al., 2013; e.g., “[Far-right group] represents values that are not compatible with [country’s] values”; 1 = *strongly disagree*, 9 = *strongly agree*); (d) support for efforts aiming to improve the lives of racial and ethnic minorities in their nations (six items generated by the research team; e.g., “To what extent do you support each of the following efforts directed at improving the situation of racial and ethnic

minorities in [country]? . . . Creating and maintaining safe spaces for minorities”; 1 = *strongly oppose*, 9 = *strongly support*).

*Demographics and other characteristics.* Participants reported their age (in years), gender, political orientation (“In general, I am . . .”; 1 = *very left-wing*, 9 = *very right-wing*), citizenship status, student affiliation, race/ethnicity, membership in the target far-right group (“Are you a member of [far-right group]?”; yes/no).

## Results

The far-right group that we focused on for each country as well as the descriptive statistics and psychometrics of the variables by country are presented in Table 2. As seen in Table 2, perceived prevalence of the far-right was significantly higher than perceived acceptability of the far-right, *t*(15) = 4.80, *p* = .002, *M*<sub>difference</sub> = 1.07, *SE* = 0.22. Anti-far-right attitudes were significantly higher than pro-far-right attitudes, *t*(15) = 6.94, *p* < .001, *M*<sub>difference</sub> = 1.43, *SE* = 0.82.

## Analytical Procedure

Participants in our sample were nested in different countries (and as an extension, nested in different universities). Although for such a design the norm is to utilize a multilevel modelling approach (see Raudenbush & Bryk, 2002), our primary analysis involved analyzing the data independently for each country using multigroup path analysis, for three reasons. First, our interest resided in testing whether the association between media exposure, perceptions of acceptability and prevalence of the far-right, and attitudes towards this movement would emerge in each country. A multilevel modelling approach would provide an estimate across all participants and groups, and would thus be unable to answer our question about country-specific variation in the hypothesized associations in each specific country. Second, even if we followed a multilevel modelling approach, our number of Level 2 groups (*n* = 15) was too low to provide a highly reliable estimate for such an effect. Third,
<table><caption>**Table 2.** Demographic information by country.</caption><thead><tr><th rowspan="2">Country</th><th rowspan="2">N<sub>total</sub></th><th rowspan="2">N<sub>female</sub></th><th rowspan="2">N<sub>male</sub></th><th rowspan="2">N<sub>other</sub></th><th>Age</th><th>Political orientation</th></tr><tr><th>M (SD)</th><th>M (SD)</th></tr></thead><tbody><tr><td>1 Australia</td><td>237</td><td>174</td><td>63</td><td>0</td><td>19.57 (3.92)</td><td>3.63 (2.14)</td></tr><tr><td>2 Austria</td><td>110</td><td>77</td><td>33</td><td>0</td><td>24.14 (5.58)</td><td>3.52 (1.34)</td></tr><tr><td>3 Belgium</td><td>164</td><td>123</td><td>39</td><td>2</td><td>18.92 (1.28)</td><td>4.40 (2.26)</td></tr><tr><td>4 England</td><td>187</td><td>158</td><td>29</td><td>0</td><td>20.16 (3.72)</td><td>3.75 (1.67)</td></tr><tr><td>5 Finland</td><td>138</td><td>100</td><td>34</td><td>4</td><td>27.43 (7.42)</td><td>2.89 (1.62)</td></tr><tr><td>6 France</td><td>376</td><td>329</td><td>44</td><td>3</td><td>19.49 (2.98)</td><td>3.89 (1.91)</td></tr><tr><td>7 Germany</td><td>199</td><td>125</td><td>73</td><td>1</td><td>22.96 (4.28)</td><td>3.54 (1.36)</td></tr><tr><td>8 Greece</td><td>216</td><td>179</td><td>35</td><td>2</td><td>22.43 (5.14)</td><td>3.92 (1.71)</td></tr><tr><td>9 Hungary</td><td>71</td><td>55</td><td>16</td><td>0</td><td>22.13 (3.41)</td><td>3.71 (2.06)</td></tr><tr><td>10 Italy</td><td>249</td><td>196</td><td>50</td><td>3</td><td>20.42 (2.16)</td><td>3.94 (1.61)</td></tr><tr><td>11 The Netherlands</td><td>151</td><td>116</td><td>35</td><td>0</td><td>19.77 (1.96)</td><td>3.96 (1.58)</td></tr><tr><td>12 Poland</td><td>166</td><td>112</td><td>50</td><td>2</td><td>22.87 (4.23)</td><td>3.96 (2.26)</td></tr><tr><td>13 Scotland</td><td>89</td><td>63</td><td>25</td><td>1</td><td>22.61 (7.43)</td><td>3.20 (1.65)</td></tr><tr><td>14 Sweden</td><td>92</td><td>61</td><td>30</td><td>1</td><td>25.75 (4.98)</td><td>3.94 (2.43)</td></tr><tr><td>15 USA</td><td>131</td><td>108</td><td>23</td><td>0</td><td>19.79 (1.35)</td><td>3.33 (1.75)</td></tr></tbody></table>

Note. Political orientation was measured on a 9-point scale, with higher scores indicating a more right-wing orientation and lower scores indicating a more left-wing orientation.

we reasoned that since the target far-right group was different for each country, conducting an analysis assuming that each outgroup is conceptually the same could be potentially misleading. Although each far-right group we selected in our study adhered to a general far-right ideology that was conceptually similar across nations, each group had its own independent agenda and history that varied greatly. Considering all these factors, we opted to report results based on a multilevel analytical approach as secondary analyses in the Supplemental Material.

To test the direct and indirect associations for our variables in each country independently, we computed a multigroup path analysis in SAS Version 9.4. In this model, media exposure to far-right movements was the exogenous variable, perceived prevalence and perceived acceptability of the far-right movement were the two parallel mediators, with pro- and anti-far-right attitudes as simultaneous outcomes (see Figure 1). Finally, we also conducted a meta-analysis to produce an overall effect across countries.

## *Multigroup Path Analysis*

We evaluated model fit based on the recommendations made by Kline (2016), which state that a model provides a good fit to the data if the chi-square value is not significant. Importantly, this value is often disregarded as it is inflated by a large sample size, which was the case for our sample. Instead, in these cases, Kline (2016) recommends evaluating model fit based on cut-off values for incremental model fit indexes. These are: CFI > .95, RMSEA < .08, and SRMR < .08. The estimated multigroup path model provided an acceptable fit to the data: $\chi^2(44) = 107.72, p < .001$, CFI = .974, RMSEA = .092, SRMR = .073. Detailed results for each country, together with the meta-analytical findings, are displayed in Table 3. Figure 2 presents a visual representation of the meta-analytical effects.

*Effects of media exposure.* Media exposure to the far-right was significantly and positively associated with perceived prevalence of this movement
in each of the 15 samples. The overall association was significant, $b = 0.28, p < .001$, 95% CI [0.24, 0.32]. Media exposure to the far-right was significantly and positively associated with perceived acceptability of the movement in only five out of 15 samples; however, the overall association was significant and in line with our hypothesis, $b = 0.06, p = .004$, 95% CI [0.02, 0.11].

*Effects of perceived prevalence of the far-right.* Perceived prevalence of the far-right was more consistently associated with anti-far-right attitudes than with pro-far-right attitudes. For anti-far-right attitudes, a significant positive association emerged in 13 out of 15 samples, while for pro-far-right attitudes, a significant negative association emerged in three out of 15 samples. Only the meta-analytical association for anti-far-right attitudes was significant (anti-far-right attitudes: $b = 0.29, p < .001$, 95% CI [0.21, 0.37]; pro-far-right attitudes: $b = -0.11, p = .056$, 95% CI [-0.22, -0.002]).

*Effects of perceived acceptability of the far-right.* Perceived acceptability of the far-right was seemingly more consistently associated with anti-far-right attitudes than with pro-far-right attitudes. For anti-far-right attitudes, a significant negative association emerged in nine out of 15 samples, while for pro-far-right attitudes, a significant positive association emerged in six out of 15 samples (five of which also showed the negative association with anti-far-right attitudes). Both meta-analytical associations were significant (anti-far-right attitudes: $b = -0.23, p < .001$, 95% CI [-0.32, -0.15]; pro-far-right attitudes: $b = 0.13, p < .001$, 95% CI [0.08, 0.18]).

*Indirect effects of media exposure on public attitudes towards the far-right.* As seen in Table 4, the indirect effects of media exposure on public attitudes towards the far-right via the mediating mechanism of perceived prevalence of the far-right (threat response) showed more consistent findings for anti- than for pro-far-right attitudes. For anti-far-right attitudes, this indirect effect was significant in 10 out of 15 samples. For

pro-far-right attitudes, the indirect effect was only significant in two samples. However, for both indirect effects, the overall effect across samples was significant (anti-far-right attitudes: $b = 0.07, p < .001$, 95% CI [0.05, 0.09]; pro-far-right attitudes: $b < -0.01, p = .040$, 95% CI [-0.06, -0.001]).

When examining the indirect effects of media exposure on public attitudes towards the far-right via the mediating mechanism of perceived acceptability of this movement (normalization response), the results were largely nonsignificant for most samples. For the media exposure → perceived acceptability of the far-right → anti-far-right attitudes pathway, only two indirect effects were significant. However, the overall indirect effect across samples was significant, $b = -0.01, p = .004$, 95% CI [-0.02, -0.002]. For the same indirect effect on pro-far-right attitudes, no indirect effect was significant. Similarly, the overall indirect effect was not significant, $b = 0.001, p = .113$, 95% CI [-0.001, 0.002].

*Exploratory analysis: Moderation by political orientation.* We considered the possibility that political orientation could moderate the associations between news consumption and perceived injunctive and descriptive norms, as well as the associations between perceived norms and pro-/anti-far-right attitudes. We tested this possibility in a multilevel path model with the interaction term between news consumption and political orientation, as well as the interaction terms between injunctive norms and political orientation, and between descriptive norms and political orientation, inserted as predictors (on the mediators and outcomes, respectively). Overall, only one interaction term was statistically significant. Specifically, there was a significant interaction between injunctive norms and political orientation on anti-far-right attitudes ($b = -0.03, p < .005$, 95% CI [-0.05, -0.02]), suggesting that for those who had a more right-wing orientation, the negative association between injunctive norms and anti-far-right attitudes was stronger. However, given the fact that all other interaction terms were not
<table><caption>**Table 3.** Path coefficients from multigroup path analysis and meta-analytic findings.</caption><thead><tr><th>Country</th><th>Media exposure →<br>Perceived acceptability<br>of far-right</th><th>Media exposure →<br>Perceived prevalence<br>of far-right</th><th>Perceived acceptability<br>of far-right → Anti-far-<br>right attitudes</th><th>Perceived prevalence<br>of far-right → Anti-far-<br>right attitudes</th><th>Perceived acceptability of<br>far-right → Pro-far-right<br>attitudes</th><th>Perceived prevalence of<br>far-right → Pro-far-<br>right attitudes</th></tr></thead><tbody><tr><td>1. Australia</td><td>-0.07 (0.05)</td><td><strong>0.28 (0.04)***</strong></td><td><strong>-0.38 (0.07)***</strong></td><td><strong>0.32 (0.08)***</strong></td><td><strong>0.18 (0.07)*</strong></td><td>-0.15 (0.08)</td></tr><tr><td>2. Austria</td><td><strong>0.19 (0.08)*</strong></td><td><strong>0.24 (0.05)***</strong></td><td>0.01 (0.07)</td><td><strong>0.31 (0.11)**</strong></td><td>-0.02 (0.08)</td><td>0.06 (0.11)</td></tr><tr><td>3. Belgium</td><td>0.10 (0.06)</td><td><strong>0.34 (0.04)***</strong></td><td>-0.14 (0.09)</td><td>0.14 (0.12)</td><td>0.09 (0.08)</td><td>0.05 (0.10)</td></tr><tr><td>4. England</td><td><strong>0.13 (0.06)*</strong></td><td><strong>0.34 (0.05)***</strong></td><td><strong>-0.39 (0.06)***</strong></td><td><strong>0.24 (0.07)***</strong></td><td><strong>0.25 (0.06)***</strong></td><td>-0.05 (0.07)</td></tr><tr><td>5. Finland</td><td>-0.04 (0.07)</td><td><strong>0.24 (0.05)*</strong></td><td><strong>-0.37 (0.10)***</strong></td><td>0.18 (0.13)</td><td><strong>0.23 (0.09)*</strong></td><td>-0.14 (0.12)</td></tr><tr><td>6. France</td><td><strong>0.15 (0.04)***</strong></td><td><strong>0.34 (0.03)***</strong></td><td><strong>-0.13 (0.04)**</strong></td><td><strong>0.19 (0.05)***</strong></td><td>0.04 (0.05)</td><td>0.08 (0.06)</td></tr><tr><td>7. Germany</td><td>-0.02 (0.05)</td><td><strong>0.16 (0.04)***</strong></td><td><strong>-0.23 (0.07)**</strong></td><td><strong>0.20 (0.10)*</strong></td><td>0.05 (0.08)</td><td>-0.15 (0.11)</td></tr><tr><td>8. Greece</td><td><strong>0.15 (0.07)*</strong></td><td><strong>0.23 (0.04)***</strong></td><td>-0.09 (0.05)</td><td><strong>0.18 (0.06)**</strong></td><td>-0.10 (0.07)</td><td>0.13 (0.09)</td></tr><tr><td>9. Hungary</td><td>-0.10 (0.10)</td><td><strong>0.36 (0.07)***</strong></td><td>-0.15 (0.12)</td><td><strong>0.43 (0.15)**</strong></td><td>0.16 (0.12)</td><td>-0.18 (0.14)</td></tr><tr><td>10. Italy</td><td><strong>0.12 (0.05)*</strong></td><td><strong>0.27 (0.03)***</strong></td><td>-0.10 (0.05)</td><td><strong>0.22 (0.08)**</strong></td><td><strong>0.15 (0.06)*</strong></td><td>-0.01 (0.08)</td></tr><tr><td>11. The Netherlands</td><td>0.04 (0.05)</td><td><strong>0.22 (0.05)***</strong></td><td>-0.14 (0.08)</td><td><strong>0.22 (0.08)**</strong></td><td>0.04 (0.07)</td><td>-0.08 (0.07)</td></tr><tr><td>12. Poland</td><td>0.13 (0.07)</td><td><strong>0.45 (0.05)***</strong></td><td><strong>-0.14 (0.07)*</strong></td><td><strong>0.60 (0.07)***</strong></td><td>0.05 (0.07)</td><td><strong>-0.57 (0.08)***</strong></td></tr><tr><td>13. Scotland</td><td>0.02 (0.08)</td><td><strong>0.27 (0.08)***</strong></td><td><strong>-0.66 (0.12)***</strong></td><td><strong>0.26 (0.11)*</strong></td><td><strong>0.50 (0.14)***</strong></td><td><strong>-0.28 (0.13)*</strong></td></tr><tr><td>14. Sweden</td><td>0.15 (0.10)</td><td><strong>0.22 (0.06)***</strong></td><td><strong>-0.38 (0.12)**</strong></td><td><strong>0.39 (0.19)*</strong></td><td><strong>0.24 (0.11)*</strong></td><td>-0.14 (0.17)</td></tr><tr><td>15. USA</td><td>0.02 (0.06)</td><td><strong>0.23 (0.06)***</strong></td><td><strong>-0.31 (0.08)***</strong></td><td><strong>0.55 (0.08)***</strong></td><td>0.17 (0.10)</td><td><strong>-0.49 (0.10)***</strong></td></tr><tr><td colspan="7"><strong>Meta-analytic results</strong></td></tr><tr><td>b</td><td>0.06</td><td>0.28</td><td>-0.23</td><td>0.29</td><td>0.13</td><td>-0.11</td></tr><tr><td>SE</td><td>0.02</td><td>0.02</td><td>0.04</td><td>0.04</td><td>0.03</td><td>0.06</td></tr><tr><td>p</td><td>.004</td><td><.001</td><td><.001</td><td><.001</td><td><.001</td><td>.056</td></tr><tr><td>95% CI</td><td>[0.02, 0.11]</td><td>[0.24, 0.32]</td><td>[-0.32, -0.15]</td><td>[0.21, 0.37]</td><td>[0.08, 0.18]</td><td>[-0.22, 0.002]</td></tr><tr><td colspan="7"><strong>Test for heterogeneity</strong></td></tr><tr><td>Q</td><td>29.01</td><td>35.65</td><td>62.38</td><td>43.99</td><td>24.14</td><td>78.31</td></tr><tr><td>p</td><td>.010</td><td><.001</td><td><.001</td><td><.001</td><td>.044</td><td><.001</td></tr></tbody></table>

Note: The values are unstandardized beta estimates; standard errors are reported within parentheses. Entries in bold were statistically significant. For the *Q* test of heterogeneity, *d* = 15. *p* < .05. **p* < .01. ***p* < .001.
<figure><img src="image_6.png" /><figcaption>**Figure 2.** Meta-analytical associations for the hypothesized model.</figcaption></figure>

*Note.* The estimates are unstandardized meta-analytic regression weights.
\*p < .05. \*\*p < .01. \*\*\*p < .001.

significant (including the coefficient for the same interaction for pro-far-right attitudes), we recommend interpreting this effect with caution.

## Discussion

Across 15 Western countries, we examined how media exposure to news coverage of the far-right was related to perceived norms and attitudes toward this movement. We found that media exposure to the far-right was consistently related to greater perceived prevalence of the far-right (i.e., perceived descriptive norms), but greater media exposure was not always related to greater perceived acceptability of the far-right (i.e., perceived injunctive norms). This suggests that seeing more instances of far-right news coverage in the media was related to believing that these groups were becoming more pervasive and commonplace in society. However, media exposure was not similarly accompanied by the sense that far-right movements were more welcomed and tolerated by others. Specifically, the association between media exposure and perceived prevalence of the far-right emerged in all 15 countries. However, the association between media exposure and perceived acceptability of the far-right emerged only in five countries (i.e., Austria, England, France, Greece, and Italy).

In addition, we found some evidence that perceived prevalence was related to less favorable attitudes toward the far-right, indicative of a threat response, whereas perceived acceptability was related to less unfavorable attitudes toward the far-right (i.e., weakening of negative attitudes), indicative of a normalization response. These divergent findings for the effects of perceived descriptive and injunctive norms on attitudes toward the far-right were in line with our recent work in the context of the Alt-Right in the US (Selvanathan & Leidner, 2022). Notably, however, comparing the findings cross-nationally, the threat response (but not the normalization response) emerged more consistently for each country.

In terms of the underlying mechanisms, we again found more consistent evidence for a threat response related to media consumption, rather than a normalization response. Media exposure was related to more unfavorable attitudes toward the far-right via greater perceived prevalence (found in 10 countries: Australia, Austria, England, France, Greece, Hungary, Italy, the Netherlands, Poland, and the US). However, there was less evidence of a link between media exposure and more favorable attitudes toward the far-right via perceived acceptability (only found in two countries: Poland and the US). This suggests that media
<table><caption>**Table 4.** Indirect effect coefficients from multigroup path analysis and meta-analytic findings.</caption><thead><tr><th>Country</th><th>Media exposure → Perceived acceptability of far-right → Anti-far-right attitudes</th><th>Media exposure → Perceived acceptability of far-right → Pro-far-right attitudes</th><th>Media exposure → Perceived prevalence of far-right → Anti-far-right attitudes</th><th>Media exposure → Perceived prevalence of far-right → Pro-far-right attitudes</th></tr></thead><tbody><tr><td>1. Australia</td><td>0.03 (0.02)</td><td>-0.01 (0.01)</td><td><strong>0.09 (0.03)***</strong></td><td>-0.04 (0.02)</td></tr><tr><td>2. Austria</td><td>0.00 (0.01)</td><td>0.00 (0.02)</td><td><strong>0.08 (0.03)*</strong></td><td>0.02 (0.03)</td></tr><tr><td>3. Belgium</td><td>-0.01 (0.01)</td><td>0.01 (0.01)</td><td>0.05 (0.04)</td><td>0.02 (0.04)</td></tr><tr><td>4. England</td><td><strong>-0.05 (0.03)*</strong></td><td>0.03 (0.02)</td><td><strong>0.08 (0.03)***</strong></td><td>-0.02 (0.02)</td></tr><tr><td>5. Finland</td><td>0.01 (0.03)</td><td>-0.01 (0.02)</td><td>0.04 (0.03)</td><td>-0.03 (0.03)</td></tr><tr><td>6. France</td><td><strong>-0.02 (0.01)*</strong></td><td>0.01 (0.01)</td><td><strong>0.06 (0.02)***</strong></td><td>0.03 (0.02)</td></tr><tr><td>7. Germany</td><td>0.01 (0.02)</td><td>0.00 (0.00)</td><td>0.03 (0.02)</td><td>-0.02 (0.02)</td></tr><tr><td>8. Greece</td><td>-0.01 (0.01)</td><td>-0.02 (0.01)</td><td><strong>0.04 (0.02)*</strong></td><td>0.03 (0.02)</td></tr><tr><td>9. Hungary</td><td>0.01 (0.02)</td><td>-0.01 (0.02)</td><td><strong>0.16 (0.06)*</strong></td><td>-0.07 (0.05)</td></tr><tr><td>10. Italy</td><td>-0.01 (0.01)</td><td>0.02 (0.01)</td><td><strong>0.06 (0.02)*</strong></td><td>0.00 (0.02)</td></tr><tr><td>11. The Netherlands</td><td>-0.01 (0.01)</td><td>0.00 (0.00)</td><td><strong>0.05 (0.02)*</strong></td><td>-0.02 (0.02)</td></tr><tr><td>12. Poland</td><td>-0.02 (0.01)</td><td>0.01 (0.01)</td><td><strong>0.27 (0.05)***</strong></td><td><strong>-0.26 (0.05)***</strong></td></tr><tr><td>13. Scotland</td><td>-0.01 (0.05)</td><td>0.01 (0.04)</td><td>0.07 (0.04)</td><td>-0.07 (0.04)</td></tr><tr><td>14. Sweden</td><td>-0.06 (0.04)</td><td>0.04 (0.03)</td><td>0.09 (0.05)</td><td>-0.03 (0.04)</td></tr><tr><td>15. USA</td><td>-0.01 (0.02)</td><td>0.00 (0.01)</td><td><strong>0.12 (0.04)**</strong></td><td><strong>-0.11 (0.04)**</strong></td></tr><tr><td colspan="5"><strong>Meta-analytic results</strong></td></tr><tr><td>b</td><td>-0.009</td><td>0.001</td><td>0.070</td><td>-0.030</td></tr><tr><td>SE</td><td>0.003</td><td>0.001</td><td>0.010</td><td>0.015</td></tr><tr><td>p</td><td>.004</td><td>.113</td><td>&lt; .001</td><td>.040</td></tr><tr><td>95% CI</td><td>[-0.02, -0.002]</td><td>[-0.0003, 0.002]</td><td>[0.05, 0.09]</td><td>[-0.06, -0.001]</td></tr><tr><td colspan="5"><strong>Test for heterogeneity</strong></td></tr><tr><td>Q</td><td>12.96</td><td>16.09</td><td>28.76</td><td>49.10</td></tr><tr><td>p</td><td>.530</td><td>.308</td><td>.011</td><td>&lt; .001</td></tr></tbody></table>

Note. The values entries are unstandardized beta estimates; standard errors are reported within parentheses. Entries in bold were statistically significant.

For the *Q* test of heterogeneity, *d* = 15.

*p* < .05. **p* < .01. ***p* < .001.

consumption of news on the far-right is more likely to be associated with an alarmed response – viewing the far-right as a threat – rather than with the normalization of their views. Thus, the purposed normalization effects of the far-right are not inevitable, as at least a portion of society may be galvanized to mobilize against this movement. The inconsistent findings around the role of perceived acceptability and a normalization

response suggest that there may be potential moderators of this effect, which we discuss below.

## *Theoretical and Applied Implications*

The current findings add to extant literature on how the media affects norms and public attitudes surrounding fringe movements. A considerable amount of research has demonstrated that
social norms can potentially sway public opinion and behaviors (McDonald & Crandall, 2015; Tankard & Paluck, 2016), however, much less work has considered the impact that everyday media exposure has on perceived norms. Moreover, there appears to be an implicit contradiction between research demonstrating that the rise of opponent groups can provoke counter-mobilization (Freel et al., 2022; Louis et al., 2010), and research demonstrating that the rise of a minority can attract emulation and conformity (Sparkman & Walton, 2017; see also Portelinha & Elcheroth, 2016), particularly by changing perceived norms (Crandall et al., 2018). Our work directly tests both possibilities by conceptualizing a threat and a normalization response to capture both potential reactions.

Integrating the media effects literature with social norms research, our findings are consistent with the agenda-setting function of the media (McCombs, 2002). Specifically, we provide direct evidence for the link between news consumption and perceived norms. This suggests that featuring far-right groups in the media is not without consequence, and may be important in shaping the normative climate of society. In our case, media exposure was related to a threat response rather than having a normalization function. The present research is consistent with the social norms approach (Lapinski & Rimal, 2005; Tankard & Paluck, 2016), which suggests that regardless of the reality of a situation, the perceptions that people hold about a situation are important in shaping their attitudes. Moreover, by contributing to an understanding of attitudes around conservative, ring-wing movements, we extend the collective action and social movements literature that has focused predominantly on progressive, left-wing movements (Simi et al., 2024; Thomas & Osborne, 2022).

Our findings also hold relevance to journalists' and political commentators' reporting on far-right groups. Routinely featuring far-right groups in news stories can have the consequence of shaping people's perceptions of reality, and even distorting them. Several commentators have warned that repeatedly featuring far-right groups in the media, even critically, may inadvertently

normalize them (Beckett, 2017; Wodak, 2020). However, our findings showed limited support for this proposition. We found considerably less evidence for a normalization response, and more consistent evidence for a threat response. Thus, bringing the far-right into the mainstream may have divergent consequences that could lead to polarization. While it could perhaps legitimize their platform and policy agenda, media coverage can also cause alarm and prompt people to mobilize against the perceived threats of the far-right. People do not merely follow along with new normative standards in society, but they also oppose and mobilize against these changes when they are perceived to be against their own values as well as broader norms within a community (see Ruisch & Ferguson, 2022). This aligns with the warnings from the United Nations Secretary-General António Guterres, who has emphasized that far-right extremism, including White supremacy and neo-Nazi groups, constitutes a “transnational threat,” and has called for “global coordinated action to defeat this grave and growing danger” (“White supremacy,” 2021).

## Limitations and Future Directions

Despite the consistency in our findings and the overall significant meta-analytical effects (and multilevel regression effects), our investigation had several noteworthy limitations. First and foremost, this research focused on Western populations and was Eurocentric by design. This by no means suggests that far-right mobilization is limited to the Western world. For example, far-right groups have gained popularity and political appeal in India, Myanmar, and Brazil (Mustaffa, 2021; Weld, 2020). It is possible that our findings will similarly apply in other regions in which the far-right has mobilized; however, the large cross-national variability observed in our study indicates that the strength of effects will undoubtedly vary. Our samples were also limited to undergraduate student populations who were largely left-leaning, which suggests that our findings may not generalize to the broader population. Future research should investigate the extent to which threat and
normalization processes occur in heterogeneous or nationally representative samples.

Relatedly, we collected data in 15 countries, which resulted in a substantial dataset, but, at the same time, implied that we could not systematically assess country-level moderators. It is possible that political conditions in certain countries make the normalization effect more prominent, while in others, a threat response is more likely. For example, factors such as country-level conflict, the current political party in power, or media freedom could shape these outcomes. These hypotheses await further empirical testing with a larger number of countries to be able to assess country-level moderation. One interesting possibility is that when the political party in power is right-wing, a normalization response is more likely because there is a perception that right-wing ideas are broadly supported (see e.g., Portelinha & Elcheroth, 2016). The specific content of the media coverage may also emerge as a potential moderator. Perhaps when mainstream media is critical of the far-right, a threat response may be more likely because of media framing effects (Nelson et al., 1997) whereby the subtle ways in which issues and stories are presented by journalists, reporters, or news anchors can influence the public's perceptions.

Although we did not find strong evidence that political orientation moderated the results, our findings may have been limited by the lack of diversity in our sample, as most participants were relatively left-leaning or progressive. A more politically diverse sample might have revealed that a threat response is stronger amongst political progressives, while a normalization response is stronger amongst political conservatives. This possibility aligns with research on political polarization, which shows that exposure to opposing views can cause partisans to become more entrenched in their preexisting views (Bail et al., 2018). For example, political progressives who are exposed to far-right ideologies may become more firmly opposed to those views, perceiving them as a greater threat. By contrast, political

conservatives may interpret the same exposure as a sign of increasing acceptance of those ideologies, thereby reinforcing their support for them.

Furthermore, our design was cross-sectional and relied exclusively on self-reports. Although this is a common approach in the literature (e.g., Calzo & Ward, 2009; Nellis & Savage, 2012; Romer et al., 2003; Vaes et al., 2015), it raises the possibility of memory bias as people may not accurately recall whether and how much they saw coverage of far-right groups in the news. Research has found that self-reported media exposure is moderately reliable (Lee et al., 2008; Scharkow, 2019). Lee et al. (2008) argue that observed associations between self-reported media exposure and outcome variables would likely be an underestimation of their true association. Building on our findings and conclusions, future investigations could link actual media coverage of focal far-right groups with surveys of public opinion (e.g., Boomgaarden & Vliegenthart, 2007). Future studies could also examine the links longitudinally, or experimentally manipulate media exposure to establish a cause–effect relationship which could solidify the potential downstream consequences that media exposure has for attitudes towards the far-right.

## Concluding Remarks

The rise of the far-right across many Western democracies means that they are increasingly featured in the media. In the present research, we examined the link between media exposure and perceived norms around the far-right, and how this relates to personal attitudes toward this movement. We found more consistent evidence for a threat response whereby media exposure was related to greater perceived prevalence, which in turn predicted more unfavorable attitudes toward the far-right. By contrast, there was considerably less evidence of a normalization response, where only in some instances, media exposure was related to greater perceived acceptability, which in turn predicted more favorable
attitudes toward the far-right. Our findings suggest that although public debate has centered on the potential normalization effects of the far-right, we should be cautious in inferring solely this outcome because of the competing and potentially stronger effects of threat.

## Acknowledgements

We would like to thank Gabriela Küchler, who assisted with the survey translation in Germany, and Evan Bottomley, who assisted with data collection in Scotland.

## Author's Note

The first four authors are listed based on their contributions to the manuscript. All other authors are listed alphabetically by last name.

## Data Availability

Data and study materials are available on the Open Science Framework (https://osf.io/n8esu/).

## Declaration of Conflicting Interests

The author(s) declared no potential conflicts of interest with respect to the research, authorship, and/or publication of this article.

## Ethical Approval and Informed Consent

This research received ethics approval from the Institutional Review Board at the University of Massachusetts Amherst, and all participants provided informed consent prior to taking part in the study.

## Funding

The author(s) received no financial support for the research, authorship, and/or publication of this article.

## ORCID iDs

Hema Preya Selvanathan https://orcid.org/0000-0002-6917-0951

Bernhard Leidner https://orcid.org/0000-0003-3315-5781

Stylianos Syropoulos https://orcid.org/0000-0001-5622-1417

Levi Adelman https://orcid.org/0000-0002-8936-9036

Maja Becker https://orcid.org/0000-0003-1187-1699

Eszter Beran https://orcid.org/0000-0001-7009-3386

Michał Bilewicz https://orcid.org/0000-0001-5027-1691

Tobias Greitemeyer https://orcid.org/0000-0002-1351-9210

Bettina Hannover https://orcid.org/0000-0003-1916-8455

Inga Jasinskaja-Lahti https://orcid.org/0000-0002-6419-5324

Peter Kardos https://orcid.org/0000-0002-8569-7809

Steve Loughnan https://orcid.org/0000-0002-4737-5120

Jeroen Vaes https://orcid.org/0000-0003-2256-2453

Martijn van Zomeren https://orcid.org/0000-0002-4873-2177

## Supplemental Material

Supplemental material for this article is available online.

## Note

1. Analyzing the data using the Germany samples as two separate groups did not change the findings.

## References

Arendt, F. (2010). Cultivation effects of a newspaper on reality estimates and explicit and implicit attitudes. *Journal of Media Psychology, 22*(4), 147–159.
https://doi.org/10.1027/1864-1105/a000020

Bail, C. A., Argyle, L. P., Brown, T. W., Bumpus, J. P., Chen, H., Hunzaker, M. B. F., Lee, J., Mann, M., Merhout, F., & Volfovsky, A. (2018). Exposure to opposing views on social media can increase political polarization. *Proceedings of the National Academy of Sciences of the USA, 115*(37), 9216–9221.
https://doi.org/10.1073/pnas.1804840115

Baugut, P., & Neumann, K. (2019). How right-wing extremists use and perceive news media. *Journalism & Mass Communication Quarterly, 96*(3), 696–720.
https://doi.org/10.1177/1077699018803080

Beckett, L. (2017, March 5). How left-wing media focus on far-right groups is helping to normalise hate. *The Guardian*. https://www.theguardian.com/world/2017/mar/05/left-wing-media-far-right-normalize-hate-trump
Bilewicz, M., & Soral, W. (2020). Hate speech epidemic. The dynamic effects of derogatory language on intergroup relations and political radicalization. *Political Psychology, 41*(S1), 3–33. https://doi.org/10.1111/pops.12670

Boomgaarden, H. G., & Vliegenthart, R. (2007). Explaining the rise of anti-immigrant parties: The role of news media content. *Electoral Studies, 26*(2), 404–417. https://doi.org/10.1016/j.electstud.2006.10.018

Brambilla, M., Sacchi, S., Pagliaro, S., & Ellemers, N. (2013). Morality and intergroup relations: Threats to safety and group image predict the desire to interact with outgroup and ingroup members. *Journal of Experimental Social Psychology, 49*(5), 811–821. https://doi.org/10.1016/j.jesp.2013.04.005

Brown, K., & Mondon, A. (2021). Populism, the media, and the mainstreaming of the far right: *The Guardian's* coverage of populism as a case study. *Politics, 41*(3), 279–295. https://doi.org/10.1177/0263395720955036

Bryant, J., & Oliver, M. B. (2009). *Media effects: Advances in theory and research*. Routledge.

Calzo, J. P., & Ward, L. M. (2009). Media exposure and viewers' attitudes toward homosexuality: Evidence for mainstreaming or resonance? *Journal of Broadcasting & Electronic Media, 53*(2), 280–299. https://doi.org/10.1080/08838150902908049

Cialdini, R. B., & Goldstein, N. J. (2004). Social influence: Compliance and conformity. *Annual Review of Psychology, 55*(1), 591–621. https://doi.org/10.1146/annurev.psych.55.090902.142015

Cialdini, R. B., Reno, R. R., & Kallgren, C. A. (1990). A focus theory of normative conduct: Recycling the concept of norms to reduce littering in public places. *Journal of Personality and Social Psychology, 58*(6), 1015–1026. https://doi.org/10.1037/0022-3514.58.6.1015

Cowan, G., Resendez, M., Marshall, E., & Quist, R. (2002). Hate speech and constitutional protection: Priming values of equality and freedom. *Journal of Social Issues, 58*(2), 247–263. https://doi.org/10.1111/1540-4560.00259

Crandall, C. S., Eshleman, A., & O'Brien, L. (2002). Social norms and the expression and suppression of prejudice: The struggle for internalization. *Journal of Personality and Social Psychology, 82*(3), 359–378. https://doi.org/10.1037/0022-3514.82.3.359

Crandall, C. S., Miller, J. M., & White, M. H. (2018). Changing norms following the 2016 U.S. presidential election: The Trump effect on prejudice. *Social*

*Psychological and Personality Science, 9*(2), 186–192. https://doi.org/10.1177/1948550617750735

Davis, L., & Deole, S. S. (2017). Immigration and the rise of far-right parties in Europe. *ifo DICE Report, 15*(4), 10–15.

de Jonge, L., & Kaufman, E. (2022). The normalization of the far right in the Dutch media in the run-up to the 2021 general elections. *Discourse & Society, 33*(6), 773–787. https://doi.org/10.1177/09579265221095418

Eberl, J.-M., Meltzer, C. E., Heidenreich, T., Herrero, B., Theorin, N., Lind, F., Berganza, R., Boomgaarden, H. G., Schemer, C., & Strömbäck, J. (2018). The European media discourse on immigration and its effects: A literature review. *Annals of the International Communication Association, 42*(3), 207–223. https://doi.org/10.1080/23808985.2018.1497452

Ekström, M., Patrona, M., & Thornborrow, J. (2020). The normalization of the populist radical right in news interviews: A study of journalistic reporting on the Swedish democrats. *Social Semiotics, 30*(4), 466–484. https://doi.org/10.1080/10350330.2020.1762984

Ellinas, A. A. (2010). *The media and the far right in Western Europe: Playing the nationalist card*. Cambridge University Press.

Europe and right-wing nationalism: A country-by-country guide. (2019, November 13). BBC News. https://www.bbc.com/news/world-europe-36130006

Forscher, P. S., & Kteily, N. S. (2020). A psychological profile of the alt-right. *Perspectives on Psychological Science, 15*(1), 90–116. https://doi.org/10.1177/1745691619868208

Freel, S. H., Bilali, R., & Godfrey, E. B. (2022). We are “the Resistance”: Predictors and consequences of self-categorization into the emerging movement to oppose Trump. *Group Processes & Intergroup Relations, 25*(2), 489–508. https://doi.org/10.1177/1368430220974758

Gallaher, C. (2020). Mainstreaming white supremacy: a twitter analysis of the American 'Alt-Right.' *Gender, Place & Culture, 28*(2), 224–252. https://doi.org/10.1080/0966369X.2019.1710472

Gattinara, C. P., & Froio, C. (2014). Discourse and practice of violence in the Italian extreme right: Frames, symbols, and identity-building in CasaPound Italia. *International Journal of Conflict and Violence, 8*(1), 154–170. https://doi.org/10.4119/ijcv-3051

Gattinara, C. P., & Froio, C. (2019). Getting “right” into the news: Grassroots far-right mobilization
and media coverage in Italy and France. *Comparative European Politics*, 17(5), 738–758. https://doi.org/10.1057/s41295-018-0123-4

Gattinara, P. C., & Pirro, A. L. P. (2019). The far right as social movement. *European Societies*, 21(4), 447–462. https://doi.org/10.1080/14616696.2018.1494301

Golder, M. (2016). Far right parties in Europe. *Annual Review of Political Science*, 19(1), 477–497. https://doi.org/10.1146/annurev-polisci-042814-012441

Hanel, P. H., & Vione, K. C. (2016). Do student samples provide an accurate estimate of the general public? *PLoS One*, 11(12), Article e0168354. https://doi.org/10.1371/journal.pone.0168354

Hansen, M. A., & Olsen, J. (2022). The Alternative for Germany (AfD) as populist issue entrepreneur: Explaining the party and its voters in the 2021 German federal election. *German Politics*, 33(4), 643–667. https://doi.org/10.1080/09644008.2022.2087871

Hogg, M. A., Turner, J. C., & Davidson, B. (1990). Polarized norms and social frames of reference: A test of the self-categorization theory of group polarization. *Basic and Applied Social Psychology*, 11(1), 77–100. https://doi.org/10.1207/s15324834basp1101_6

Hornsey, M. J., Majkut, L., Terry, D. J., & McKimmie, B. M. (2003). On being loud and proud: Non-conformity and counter-conformity to group norms. *British Journal of Social Psychology*, 42(3), 319–335. https://doi.org/10.1348/014466603322438189

Iyer, A., Schmader, T., & Lickel, B. (2007). Why individuals protest the perceived transgressions of their country: The role of anger, shame, and guilt. *Personality and Social Psychology Bulletin*, 33(4), 572–587. https://doi.org/10.1177/0146167206297402

Kallgren, C. A., Reno, R. R., & Cialdini, R. B. (2000). A focus theory of normative conduct: When norms do and do not affect behavior. *Personality and Social Psychology Bulletin*, 26(8), 1002–1012. https://doi.org/10.1177/01461672002610009

Kline, R. B. (2016). *Principles and practice of structural equation modelling* (4th ed.). Guilford Press.

Lapinski, M. K., & Rimal, R. N. (2005). An explication of social norms. *Communication Theory*, 15(2), 127–147. https://doi.org/10.1111/j.1468-2885.2005.tb00329.x

Lees, C. (2018). The “Alternative for Germany”: The rise of right-wing populism at the heart of Europe. *Politics*, 38(3), 295–310. https://doi.org/10.1177/0263395718777718

Leets, L. (2001). Explaining perceptions of racist speech. *Communication Research*, 28(5), 676–706. https://doi.org/10.1177/009365001028005005

Lee, C. J., Hornik, R., & Hennessy, M. (2008). The reliability and stability of general media exposure measures. *Communication Methods and Measures*, 2(1–2), 6–22. https://doi.org/10.1080/19312450802063024

Louis, W. R., Duck, J. M., Terry, D. J., & Lalonde, R. N. (2010). Speaking out on immigration policy in Australia: Identity threat and the interplay of own opinion and public opinion. *Journal of Social Issues*, 66(4), 653–672. https://doi.org/10.1111/j.1540-4560.2010.01669.x

Lubbers, M., & Coenders, M. (2017). Nationalistic attitudes and voting for the radical right in Europe. *European Union Politics*, 18(1), 98–118. https://doi.org/10.1177/1465116516678932

Lubbers, M., Gijsberts, M., & Scheepers, P. (2002). Extreme right-wing voting in Western Europe. *European Journal of Political Research*, 41(3), 345–378. https://doi.org/10.1111/1475-6765.00015

Masser, B., & Phillips, L. (2003), “What Do Other People Think?”— The role of prejudice and social norms in the expression of opinions against gay men. *Australian Journal of Psychology*, 55(3), 184–190. https://doi.org/10.1080/0004953042000298652.

McCombs, M. (2002). *The agenda-setting role of the mass media in the shaping of public opinion* [Paper presentation]. Mass Media Economics 2002 Conference, London School of Economics, London, UK. Available at: https://sticerd.lse.ac.uk/dps/extra/McCombs.pdf

McDonald, R. I., & Crandall, C. S. (2015). Social norms and social influence. *Current Opinion in Behavioral Sciences*, 3, 147–151. https://doi.org/10.1016/j.cobeha.2015.04.006

Mendes, M. S., & Dennison, J. (2021). Explaining the emergence of the radical right in Spain and Portugal: Salience, stigma and supply. *West European Politics*, 44(4), 752–775. https://doi.org/10.1080/01402382.2020.1777504

London, A., & Winter, A. (2020). *Reactionary democracy: How racism and the populist far right became mainstream*. Verso Books.

Mudde, C. (2007). *Populist radical right parties in Europe*. Cambridge University Press.

Mudde, C. (Ed.). (2016). *The populist radical right: A reader*. Taylor & Francis.
Mustaffa, M. (2021, July 14). *Right-wing extremism has deep roots in Southeast Asia*. Global Network on Extremism & Technology. https://gnet-research.org/2021/07/14/right-wing-extremism-has-deep-roots-in-southeast-asia/

Nelson, T. E., Clawson, R. A., & Oxley, Z. M. (1997). Media framing of a civil liberties conflict and its effect on tolerance. *American Political Science Review*, *91*(3), 567–583. https://doi.org/10.2307/2952075

Nellis, A. M., & Savage, J. (2012). Does watching the news affect fear of terrorism? The importance of media exposure on terrorism fear. *Crime & Delinquency*, *58*(5), 748–768. https://doi.org/10.1177/0011128712452961

Norris, P., & Inglehart, R. (2019). *Cultural backlash: Trump, Brexit, and authoritarian populism*. Cambridge University Press.

Pahnke, A. (2021, March 31). *How the far right got a stranglehold on the West*. Aljazeera. https://www.aljazeera.com/features/2021/3/31/how-the-far-right-got-a-stranglehold-on-the-west

Ponce de Leon, R., Rifkin, J. R., & Larrick, R. P. (2022). "They're everywhere!": Symbolically threatening groups seem more pervasive than nonthreatening groups. *Psychological Science*, *33*(6), 957–970. https://doi.org/10.1177/09567976211060009

Portelinha, I., & Elcheroth, G. (2016). From marginal to mainstream: The role of perceived social norms in the rise of a far-right movement. *European Journal of Social Psychology*, *46*: 661–671. https://doi.org/10.1002/ejsp.2224.

Raudenbush, S. W., & Bryk, A. S. (2002). *Advanced quantitative techniques in the social sciences: Vol. 1. Hierarchical linear models: Applications and data analysis methods*. Sage.

Rettie, R., Burchell, K., & Barnham, C. (2014). Social normalisation: Using marketing to make green normal. *Journal of Consumer Behaviour*, *13*(1) 9–17. https://doi.org/10.1002/cb.1439

Riek, B. M., Mania, E. W., & Gaertner, S. L. (2006). Intergroup threat and outgroup attitudes: A meta-analytic review. *Personality and Social Psychology Review*, *10*(4), 336–353. https://doi.org/10.1207/s15327957pspr1004_4

Romer, D., Jamieson, K. H., & Aday, S. (2003). Television news and the cultivation of fear of crime. *Journal of Communication*, *53*(1), 88–104. https://doi.org/10.1111/j.1460-2466.2003.tb03007.x

Roussos, G., & Dovidio, J. F. (2019). Enhancing the salience of free speech rights increases differential perceived free speech protections for criminal

acts against Black versus White targets. *Journal of Applied Social Psychology*, *49*(8), 519–533. https://doi.org/10.1111/jasp.12601

Rozado, D., & Kaufmann, E. (2022). The increasing frequency of terms denoting political extremism in US and UK news media. *Social Sciences*, *11*(4), Article 167. https://doi.org/10.3390/socsci11040167

Ruisch, B. C., & Ferguson, M. J. (2022). Changes in Americans' prejudices during the presidency of Donald Trump. *Nature Human Behaviour*, *65*(5), 656–665. https://doi.org/10.1038/s41562-021-01287-2

Rydgren, J. (2007). The sociology of the radical right. *Annual Review of Sociology*, *33*, 241–262. https://doi.org/10.1146/annurev.soc.33.040406.131752

Rydgren, J. (Ed.). (2018). *The Oxford handbook of the radical right*. Oxford University Press.

Scharkow, M. (2019). The reliability and temporal stability of self-reported media exposure: A meta-analysis. *Communication Methods and Measures*, *13*(3), 198–211. https://doi.org/10.1080/19312458.2019.1594742

Selvanathan, H. P., & Leidner, B. (2022). Normalization of the Alt-Right: How perceived prevalence and acceptability of the Alt-Right is linked to public attitudes. *Group Processes & Intergroup Relations*, *25*(6), 1594–1615. https://doi.org/10.1177/13684302211017633

Simi, P., Futrell, R., & Burston, A. (2024). How threat mobilizes the resurgence and persistence of US White supremacist activism: The 1980s to the present. *Annual Review of Sociology*, *50*(1), 297–317. https://doi.org/10.1146/annurev-soc-031021-112151

Skitka, L. J., Bauman, C. W., & Mullen, E. (2004). Political tolerance and coming to psychological closure following the September 11, 2001, terrorist attacks: An integrative approach. *Personality and Social Psychology Bulletin*, *30*(6), 743–756. https://doi.org/10.1177/0146167204263968

Smith, J. R., & Terry, D. J. (2003). Attitude-behaviour consistency: The role of group norms, attitude accessibility, and mode of behavioural decision-making. *European Journal of Social Psychology*, *33*(5), 591–608. https://doi.org/10.1348/014466600164534

Soral, W., Bilewicz, M., & Winiewski, M. (2018). Exposure to hate speech increases prejudice through desensitization. *Aggressive Behavior*, *44*(2), 136–146. https://doi.org/10.1002/ab.21737
Soral, W., Liu, J., & Bilewicz, M. (2020). Media of contempt: Social media consumption predicts normative acceptance of anti-Muslim hate speech and Islamoprejudice. *International Journal of Conflict and Violence, 14*, 1–13. https://doi.org/10.4119/IJCV-3774

Sparkman, G., & Walton, G. M. (2017). Dynamic norms promote sustainable behavior, even if it is counter-normative. *Psychological Science, 28*(11), 1663–1674. https://doi.org/10.1177/0956797617719950

Tankard, M. E., & Paluck, E. L. (2016). Norm perception as a vehicle for social change. *Social Issues and Policy Review, 10*(1), 181–211. https://doi.org/10.1111/sipr.12022

Terman, R. (2020). The positive side of negative identity: Stigma and deviance in backlash movements. *The British Journal of Politics and International Relations, 22*(4), 619–630. https://doi.org/10.1177/1369148120948485

Thomas, E. F., & Osborne, D. (2022). Protesting for stability or change? Definitional and conceptual issues in the study of reactionary, conservative, and progressive collective actions. *European Journal of Social Psychology, 52*(7), 985–993. https://doi.org/10.1002/ejsp.2912

Turner, J. C., & Reynolds, K. J. (2012). Self-categorization theory. In P. A. M. Van Lange, A. W. Kruglanski, & E. T. Higgins (Eds.), *Handbook of theories of social psychology* (Vol. 2, pp. 399–417). Los Angeles, CA: Sage. doi:10.4135/9781446249222.n46

Vaes, J., Latrofa, M., Vieno, A., & Pastore, M. (2015). Exposure to politicized media and prejudice against immigrants in Italy: Identifying its impact and psychological mediators. *Psicologia Sociale, 10*(2), 141–160. https://doi.org/10.1482/80762

Van Klingeren, M., Boomgaarden, H. G., Vliegenthart, R., & De Vreese, C. H. (2015). Real world is not enough: The media as an additional source of negative attitudes toward immigration, comparing Denmark and the Netherlands. *European Sociological Review, 31*(3), 268–283. https://doi.org/10.1093/esr/jcu089

Van Spanje, J., & Van Der Brug, W. (2007). The party as pariah: The exclusion of anti-immigration parties and its effect on their ideological positions. *West European Politics, 30*(5), 1022–1040. https://doi.org/10.1080/01402380701617431

Wakefield, M. A., Loken, B., & Hornik, R. C. (2010). Use of mass media campaigns to change health behaviour. *The Lancet, 376*(9748), 1261–1271. https://doi.org/10.1016/S0140-6736(10)60809-4

Walgrave, S., & De Swert, K. (2004). The making of the (issues of the) Vlaams Blok. *Political Communication, 21*(4), 479–500. https://doi.org/10.1080/10584600490522743

Walgrave, S., & Vliegenthart, R. (2012). The complex agenda-setting power of protest: Demonstrations, media, parliament, government, and legislation in Belgium, 1993–2000. *Mobilization: An International Quarterly, 17*(2), 129–156. https://doi.org/10.17813/maiq.17.2.pw053m281356572h

Weld, K. (2020). Holy war: Latin America's far right. *Dissent Magazine*. https://www.dissentmagazine.org/article/holy-war-latin-americas-far-right/

White, M. H., II, & Crandall, C. S. (2017). Freedom of racist speech: Ego and expressive threats. *Journal of Personality and Social Psychology, 113*(3), 413–429. https://doi.org/10.1037/pspi0000095

White supremacy a “transnational threat,” U.N. chief warns. (2021, February 23). Reuters. https://www.reuters.com/article/world/white-supremacy-a-transnational-threat-un-chief-warningsidUSKBN2AM1PF/

Wilkins, C. L., & Kaiser, C. R. (2014). Racial progress as threat to the status hierarchy: Implications for perceptions of anti-White bias. *Psychological Science, 25*(2), 439–446. https://doi.org/10.1177/0956797613508412

Wodak, R. (2020). *The politics of fear: The shameless normalization of far-right discourse*. Sage.

Yan, H. Y. (2019). “The rippled perceptions”: The effects of LGBT-inclusive TV on own attitudes and perceived attitudes of peers toward lesbians and gays. *Journalism & Mass Communication Quarterly, 96*(3), 848–871. https://doi.org/10.1177/1077699018821327