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Does Peer Socialization Within Cohorts Foster Political Attitudes? A Longitudinal Study of Elite Business Students

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  • 28-10-2024
  • Original Paper
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Abstract

The article explores the role of peer socialization in shaping political attitudes among elite business students, using a longitudinal study across four prestigious business schools in Sweden and Finland. It investigates whether increased social interactions lead to convergence in political attitudes and tests this hypothesis using both cross-sectional and panel data analyses. The study finds no significant evidence supporting the peer socialization effect, challenging the prevailing notion that university attendance causally influences political attitudes through peer interactions. This nuanced finding contributes to the broader understanding of political socialization processes in higher education.

Supplementary Information

The online version contains supplementary material available at https://doi.org/10.1007/s11109-024-09978-y.

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Springer Nature remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.

Introduction

Getting a university education is a defining experience in a person’s life and scholars suggest that it can foster distinct political attitudes and electoral behaviors (Stubager, 2008). Yet, despite the considerable interest in the impact of education on political attitudes, surprisingly little is known about the underlying mechanism that drives the association. It is still an open question whether the correlation is causal, and if so, what the underlying mechanism is (see e.g., d'Hombres & Nunziata, 2016; Campbell & Horowitz, 2016). Previous research into the association between education and political attitudes suggests that informal peer socialization in comparatively elite milieus is one of the most probable mechanisms in the case of a 'higher education effect’ (Apfeld et al., 2022; Stubager, 2008; Surridge, 2016). Students may uphold and transmit social norms about how to think and act politically (Mendelberg et al., 2017). The characteristics of the peers would therefore shape both the intensity of the socialization and the salient issues within the cohort. Accordingly, variations in student compositions might account for why certain studies identify a causal effect of attending university on political attitudes (e.g., Scott, 2022), whereas others do not (e.g., Simon, 2022).
The idea of an inter-group transmission of attitudes within university cohorts has, however, rarely been systematically investigated due to limitations in data availability on students’ social interactions. Instead, the assumption of a peer socialization effect is the outcome of an empirical exclusion of other potential explanations (e.g., Scott, 2022; Stubager, 2008; Surridge, 2016) or is based in data from over 30 years ago (Dey, 1996; Pascarella and Terenzini, 1991). Even if some studies investigate political socialization within smaller friendship groups (Algan et al., 2023; Hjerm et al., 2018) or between college roommates (Strother et al., 2021), there is a need for research on broader political socialization processes in higher education. Indeed, if peer socialization is a partial driver of the education divide, where highly educated tend to hold more liberal preferences, it is probable that socialization at this phase of an individual’s education and at this group level would answer to such attitudinal differences. Only Mendelberg et al. (2017) succeed in identifying a causal effect of social norms in university classes on students’ political attitudes in their novel U.S. study while focusing on students’ economic preconditions. This paper studies the peer socialization mechanism with a different research design and context, utilizing more detailed measurements of social behavior as well as an objective reduction of socialization due to the Covid-19 pandemic’s social restrictions. It further theorizes and investigates attitudinal distributions within university cohorts rather than solely looking at a directional attitudinal change to more closely align with research on socialization effects (see Dey, 1996). This paper examines the question: Does peer socialization in higher education influence political attitudes?
We employ a longitudinal network study of four top-ranked business schools in Sweden and Finland. These prestigious educational institutions encourage and facilitate social interactions among the students (Tyllström et al., 2022), increasing the possibility of detecting a socialization effect in this environment. The empirical analysis of the data consists of three parts. First, the study descriptively examines the distribution of attitudes within cohorts over time cross-sectionally, where convergence indeed is an expected outcome given the hypothesis of socialization effects. Second, an ordinary least square (OLS) regression examines the association between students’ social life and their deviation from the average attitude in their cohort. Through this analysis, it is possible to directly examine whether students with various extents of social interactions are closer to the majority norms in class. Third, the study adopts the Covid-19 pandemic as an exogenous shock to political socialization among peer networks in a two-wave panel, allowing for a difference-in-difference design to test the influence of peers on attitude formation causally. The rationale behind this ‘treatment’ is the fact that some cohorts randomly experienced their education online during the pandemic and were recommended social distancing. In this study, we thus extend previous research in several ways. We use a unique longitudinal network dataset of undergraduate business students studying at prestigious universities, covering both their extent of social interactions and their experience of social life within the cohort. We also expand the methodological approach to study socialization effects by examining the impact of social interactions through two avenues: initially, by analyzing students’ self-reported social behaviors, and subsequently, by leveraging an external shock affecting such socialization.
Contrary to expectations of convergence, this study does not yield support for the presence of peer socialization effects on attitude formation. There are no signs of attitude convergence over time and little evidence to support that different social behaviors are associated with more conforming political attitudes. Even worse for the possibility to support a peer socialization mechanism, the results from the difference-in-difference design show that there are no significant differences between cohorts studying on campus or online. While the paper’s design only enables us to make causal claims about the socialization mechanism, the descriptive findings are consistent with the notion of an overall attitudinal change resulting from university attendance. Consequently, we conclude that if participation in higher education indeed has an overall causal effect on political attitudes, peer socialization at the cohort level is unlikely the driving force behind it. The study thereby nuances the notion of the underlying mechanism of the 'higher education effect’, which is of critical interest given the increasing role of education as a predictor for political preferences in advanced democracies (Bornschier et al., 2021). In addition, these insights contribute to an even broader question of how, when and for whom political socialization processes operate. We close the paper by discussing the general implications of the results and suggest future studies to move the field forward.

Higher Education and Political Attitudes

Despite the robust and consistent association between higher education and political attitudes (Marshall, 2016; Stubager, 2008), a large body of research questions the notion of a causal effect of university attendance. The relative importance of self-selection into higher education is the subject of considerable discussion. Pre-adult factors such as parental socialization, family socioeconomic status, genetics, and intelligence may cause individuals to develop certain attitudes as well as attend higher education (Campbell & Horowitz, 2016; Persson, 2015; Weinschenk et al., 2021). However, while recent research backs up the ‘null hypothesis’ of the education-attitudes link (e.g., Finseraas et al., 2018; Kunst et al., 2020; Lancee & Sarrasin, 2015; Simon, 2022; Miragaya et al., 2023), several studies with equally strong research designs for identifying a causal effect of higher education do support the idea of attitude formation through university attendance (e.g., Scott, 2022; Marshall, 2016; Cavaille & Marshall, 2019; d'Hombres & Nunziata, 2016; Mendelberg et al., 2017).
If the first question occupying the literature on education effects concerns the causality of the effect, the second question concerns the underlying mechanism that may change individuals’ political attitudes while in education. Although such attitudinal change could result from an increased cognitive sophistication that occurs in parallel with an individual’s studies (Nie et al., 1996), the model of explanation with the most considerable support in the literature relates to universities as a site for interpersonal socialization (see e.g., Stubager, 2008). This socialization mechanism is based on one central idea: through education, individuals internalize the values they encounter in the university milieu through interpersonal interactions (Dey, 1996; Mendelberg et al., 2017; Nickerson, 2009). The social influence on attitude formation has proven central in other realms of an individual’s life. Discussion partners may influence political attitudes (Huckfeldt & Sprague, 1991; however, see Farrar et al., 2009), and family socialization during childhood has long-lived effects on individuals’ political views (Rekker et al., 2017). If university attendance indeed changes political attitudes, it is thus not unlikely that socialization is the main driver behind it.
Empirically, the works of Dey (1996), Paterson (2009), Stubager (2008), Scott (2022) and Surridge (2016) all suggest (informal) processes of socialization on educational campuses as the main driver of the linkage between education and political attitudes. While suggestive evidence indicates that professors may also serve as socializing agents (Apfeld et al., 2022; Gross & Fosse, 2012), peers can be the most important attitudinal influences. Students transmit norms on campuses about what are socially accepted political preferences.1 As such, Simon (2022) posits that the divergent conclusions from her and Scott’s (2022) studies, both studying if there is a causal effect of education on British students, could be attributed to the varying student group compositions across the time periods they examined. In the realm of peer socialization, both the direction of attitudinal change and the convergence of attitudes are thus of interest. While much of the extensive literature in political science primarily focuses on the liberalizing effect of education and posits peer socialization as a possible driver of such change (Stubager, 2008; Surridge, 2016), socialization literature suggests that peer transmission of attitudes rather tends to make attitudes more similar (Dey, 1996).
The socialization mechanism is mainly confirmed by the exclusion of other potential explanations and does not directly consider students’ social interactions and behaviors (Scott, 2022; Stubager, 2008; Surridge, 2016). Due to the inability to control for all possibly important confounders, and the risk of measurement errors in the data collected through surveys (as noted by Simon, 2022, and Campbell & Horowitz, 2016), these studies could overestimate the influence of peer socialization. Only a few studies have attempted to identify the impact of socialization processes in the university milieu using sophisticated quantitative techniques. As such, research indicates that students randomly assigned to live together as roommates, an intense socializing experience, tend to become more politically alike rather than necessarily more liberal throughout their studies (Strother et al., 2021). Interestingly, Strother et al. (2021) did not identify a causal effect of university attendance when examining a general shift in attitudes among the students. In addition, Mendelberg et al. (2017) show that a student’s values may be influenced by their peer group’s economic views and consumption behavior (see also Newcomb, 1943; Pascarella and Terenzini, 1991), and may even move students in a conservative direction.
While the influence of roommates and smaller friendship groups highlights the impact of close relationships on attitude formation, the effects of class norms on attitudes do not need to be limited to close ties (Newcomb, 1943). In fact, if peer socialization in universities would explain parts of the ‘higher education effect’, cohorts should be the units of interest. Only Mendelberg et al. (2017) have collected data on ideological class composition and political attitudes providing unbiased estimates on the impact of class norms. Their data structure allows for examinations of school class characteristics and attitude formation, but detailed information about the social experiences within school classes is lacking. It further remains uncertain whether the conclusions drawn from their research apply to students from other countries with less politically polarized climates (Boxell et al., 2022). Colleges in the United States are further known for their high admission fees (Garritzman, 2016), which are likely to impact the characteristics of the higher education entrants and the overall campus experience. We thus aim to investigate a distinct case of student sample in the form of business students in Sweden and Finland. Furthermore, we aim to bridge these two bodies of literature by placing a primary emphasis on the convergence of attitudes while also acknowledging the significance of the direction of possible attitudinal change.

The Case of Business Students

Scholars have taken a particular interest in the socialization effects of business education since at least Schein’s (1967) seminal study demonstrating that students’ political views tend to align with those of their teachers over time. This interest is primarily due to the fact that business graduates tend to be important actors in society because of their higher propensity to join the economic and political elite (Rivera, 2016). At the same time, studies show that business students have different ethical standards and put a higher value on materialistic values (Sagiv & Schwartz, 2000), compared to students from other fields (Vedel & Thomsen, 2017). Since one central hypothesis is that this could be due to socialization through the content of the education (Anteby, 2013), many schools have taken care to include modules on corporate social responsibility (CSR), business ethics, and responsible management education (RME) and the like, although a recent review shows that most extant studies are in favor of a self-selection effect (Miragaya-Casillas et al., 2023).2 These studies tend to focus on moral values rather than political attitudes, but suggestive evidence indicates that studying economics (a core discipline in business programs) makes students more market liberal (cf. Fischer et al., 2017; see also Haski-Leventhal et al. 2022).
If, on the other hand, the attitude development of students results from peer socialization, this is likely to be especially prevalent in business programs since they emphasize the importance of social networks and facilitate social activities within cohorts to a higher extent than other educational programs (Schleef, 2005). This results from the fact that the future career trajectories of the students may depend on their ability to network effectively and be socially accepted (de Janasz & Forret, 2008; Tyllström et al., 2022). The specific educational environment thereby creates an ideal setting for detecting peer effects. High-status environments, such as prestigious educational institutions, further tend to be formative for individuals and an important marker of social identities (e.g., Tajfel & Turner, 1986). This is especially true in this study, as the student sample is comparatively homogeneous, thereby enhancing the likelihood of a stronger sense of identification among peers (McPherson et al., 2001). However, given the goal-oriented and determined nature of the students attending, they may hold a higher attitude stability than other students (Vedel & Thomsen, 2017). The students may thereby be prone to strong selection effects that could reduce the impact of a socialization, but the opposite could also be true: their ambition might make social conformity even more crucial for them.

Theoretical Expectations: Peer Socialization

According to the assumptions of a peer socialization effect, attitudinal change during an educational trajectory occur as students internalize the political attitudes they encounter in order to fit in with the peer group (Stubager, 2008). However, even though the correlation between education and liberal attitudes is widespread and the socialization thus assumed to be directional (Scott, 2022; Simon, 2022; Stubager, 2008), there are no theoretical reasons based on the socialization literature for the attitudinal change to necessarily be liberalizing (Mendelberg et al., 2017; Newcomb, 1943). As discussed, the underlying assumption of socialization effects is rather that attitudes are more likely to align with the specific cohort’s social norms (cf. Strother et al., 2021). The composition of students will thus influence the values that prevail in the classroom (Mendelberg et al., 2017; Ricart-Huguet & Paluck, 2023). It is therefore reasonable to expect a decrease in attitudinal differences in university cohorts over time, as students who hold non-conforming attitudes are more likely to shift their beliefs to conform with the majority, resulting in less variability between students. Students who already lie close to the majority views may not experience attitudinal change, while students who hold more deviating attitudes could be expected to experience attitudinal change and converge toward the majority norms.
Furthermore, central to the transmittance of attitudes is social embeddedness since it directly or indirectly exposes students to the social norms in class (Mendelberg et al., 2017; Newcomb, 1943). Social groups can require specific attitudes for social acceptance and sanction ‘illegitimate’ behaviors and attitudes (Newcomb, 1943). Additionally, indirect social comparison processes can also influence attitudes. For instance, students may view others at the same level and within the same field of education as their reference group and adjust their opinions on salient issues to conform to those of the prototypical group member (Westholm, 1999). This process does not necessarily involve direct social sanctions, nor does it assume close ties to individuals in that particular group. The effect of education may thereby solely appear for students who are frequently exposed to the norms prevailing within the cohort. Students who are not engaging with their peers would accordingly be less likely to experience an attitudinal change, while students who socialize with their peers would be more likely to conform to the majority views. This paper will therefore operate under the following hypotheses:
H (1):
Political attitudes among students in a cohort become more similar over time.
H (2):
There is a stronger convergence in attitudes among socially embedded students than for those who do not engage with their peers.

Method

Material

We collected data from students at four top business schools in Sweden and Finland.3 The schools are either independent business schools or have a well-defined business unit within the university. The data collection covers four cohorts throughout their studies. Two of them, Hanken School of Economics (Finland) and Stockholm School of Economics (Sweden) are considered elite (business) schools since they are highly selective, consistently top-ranked academically, and small in size (Van Zanten, 2009). The other two schools (School of Business, Economics and Law at the University of Gothenburg and Industrial Economics at KTH) are parts of larger universities, but they are independent institutions with likewise selective programs that are relatively small. Due to these features, these schools also provide and encourage a social network that allows for gaining more social capital.
The first cohort enrolled in September 2019 and completed their studies in June 2022, while the second cohort began in September 2020 and graduated in June 2023. The third and fourth cohorts started their studies in 2021 and 2022, respectively. The total sample of observations is 2651. In October each year, the students were sent a web-based survey that included questions about their social interactions and political attitudes. While the survey’s focus is directed at their social networks in and outside school, it also include socio-demographic background factors such as their family background. In addition, it allows us to make comparisons between the attitudes of cohorts with various extents of social interactions: the cohort that was the most affected by the pandemic (the 2020 cohort) and a cohort that initially could engage in student life at campuses (the 2019 cohort). However, although the survey was distributed annually, only a subset of students consistently responded to it over multiple years. To maintain an adequately large sample size, tests one and two, therefore, employ cross-sectional analyses. These analyses are also conducted on the students who engaged in the survey for multiple years and these results are placed in the appendix. Conversely, test three investigates shifts in attitudes among students who completed the survey two consecutive years before and during the pandemic, as a two-wave panel.

Operationalization

Dependent Variable

Two major conflict lines shape the electoral landscape in post-industrial societies. The traditional economic conflict line concerns the dynamic between the state and the market, while the sociocultural conflict line commonly is characterized by attitudes that relate to struggles over borders and authorities (Bornschier et al., 2021; Stubager, 2008). This study examines economic and sociocultural political attitudes and how education may foster them. While sociocultural attitudes such as immigration are highly salient in the political context and are thereby expected to be discussed on campuses (Stubager, 2008), issues related to the state and market might be particularly salient in the context of business schools (Haski-Leventhal et al., 2022).
Two of the four variables of interest relate to conventional economic issues, including attitudes toward reducing taxes and allowing dividends in welfare systems. The other two focus on sociocultural issues, namely attitudes towards accepting more refugees and promoting women quotas. Responses to these issues are rated on a scale of 1 to 5, where higher values indicate more favorable attitudes toward the issue.4 The survey questions are formulated as follows: “Below are a number of proposals which have emerged during the political debate. What is your opinion on each one of them?” with specific sub questions: (1) Allow more refugees to enter the country you live in, (2) Paying dividends should not be permitted in publicly funded healthcare, school, and social care,5 (3) Reduce taxes, and (4) Apply quotas to increase the proportion of women on company boards. In parts of the analyses, we concentrate on the majority norms in the cohort and do not consider nor theorize the specific direction of the political attitudes to align with the expectations of a peer-socialization mechanism.6 Analyses of the linear relationship with the attitudes at the Likert scale as the dependent variables are placed in the appendix. The focal relationship is thus between social behavior and the absolute deviation between the individuals’ political attitude and the average political attitude in their school and cohort. Positive coefficients represent a greater difference from the attitudinal mean in the cohort.

Social Life

We explore the relationship between social embeddedness using two main measures. The first measure assesses the frequency of social interactions among peers. The scale ranges from 1 (less frequently than monthly) to 5 (several times per day) for the students’ peers in their class. The measure is constructed as an index and standardized to range between 1 and 10. In the main analyses, the index is divided into a categorical variable with three levels of social engagement: low, medium, and high. This categorization is further based on theoretical expectations as the effect may be non-linear. Students who do not engage with their peers at all are unlikely to experience attitudinal change. In turn, the most sociable students are the most embedded and could therefore be expected to undergo attitudinal change, but they may act as leaders and thus be the ones that influence the attitudes of others (see e.g., Gnambs & Batinic, 2012).
The study encompasses three variables that capture the experience of the social dimensions of the students’ lives. These concerns: (1) whether one feels anonymous in their school, (2) if there are too many social activities in the class, and (3) if they have an easy time making friends in school.7 Like the variables measuring political attitudes, the values of the variables range between 1–5. Higher values correspond to more significant difficulties in the social aspects of the students’ lives.

Control Variables

The models include controls for gender, as studies indicate that socializing behaviors may differ between men and women (Mengel, 2020; Woehler et al., 2021). In addition, age is included since it is likely that older students socialize less with their peers in class than younger individuals. Parents’ levels of education are utilized as a robustness check for social class, ranging between 1–4, where higher values equal to more well-educated parents. As previously discussed, self-selection mechanisms are likely prevalent in all studies of higher education (e.g., Lancee and Sarrassin, 2015), and controls for social background reduce the risks of this important confounder. Given that this study focuses on students, conventional socio-economic background controls such as income, are not applicable. See table A1 in the appendix for summary statistics over the variables.

Studies

Identifying the influence of peer socialization on opinion formation processes is exceedingly difficult as several omitted variables could drive potential outcomes. Therefore, we propose a research design to investigate the transmission mechanism that is based on three studies, each of which contributes independently to examining socialization effects. The studies have a complementary nature due to their distinct strengths and limitations as explained below.
First, we examine differences in attitude variance between cohorts who have studied for varying durations, ranging from 1 to 3 years. Test 1 is conducted both in a cross-sectional form (as shown in the main manuscript) and in a panel (as shown in the appendix). This analysis allows us to descriptively observe attitudinal differences between the cohorts and preserves a full sample size. This stage of the analysis thereby offers an initial overview of whether attitudes tend to be more alike among students in more advanced stages of their educational trajectory. However, it does not examine the impact of their diverse socializing behaviors directly. Therefore, we leverage survey data with information about the students’ political attitudes and social life in an OLS regression analysis in the next step. Through this analysis, it is possible to observe the relationship between students’ self-reported social behaviors and their attitudes. Still, causal conclusions cannot be inferred from ‘conventional’ regression-based studies, which only identify associations (Simon, 2022). In addition, since the way one maintains and creates social contacts could be considered a sensitive topic, it is not unlikely that social desirability bias will interfere with the results. The study, therefore, takes advantage of the restrictions on social interactions amongst peer networks during the Covid-19 pandemic. Test 3 compares changes in political attitudes between the cohort that started studying during the pandemic and whose social networks were seriously affected to the cohort that started studying before the pandemic. Test 3 thereby utilizes the panel structure of the data and an externally imposed reduction of peer socialization, although with a smaller sample. Taken together, the first study tests H (1) concerning convergence in attitudes within cohorts over time, whilst the second and third studies test H(2) whether the social behaviors of students influence their attitudinal similarity.

Test 1

The first study concentrates on the distribution of attitudes over time. Convergence within university cohorts would align with the expected effects of socialization.
Table 1 presents the means and standard deviations at the three points in time: students studying the first, second, or third year of their program. The results indicate significant differences in attitude mean across the student groups for three of the four attitudes, as demonstrated by t-tests. Students studying their third year are generally more in favor of allowing refugees and forbidding welfare dividends, while being slightly more negative towards reducing taxes. The attitudinal direction aligns well with studies of the ‘higher education effect’ (see e.g., Stubager, 2008), although more negative attitudes towards the market in the case of welfare dividends is not in the expected direction of students studying economics and business (see Fischer et al., 2017).8 While these descriptive results are consistent with the notion of attitudinal change from university attendance, the differences in standard deviations across the groups provide less support for the notion of socialization effects. The distribution of attitudes remains largely unchanged across all issues. Furthermore, Table A2 shows the analysis on the students included in the two-wave panel and report striking attitudinal stability, although on a smaller sample size. Figure 1 below displays histograms representing the distribution of the variables for the three groups and the seemingly lack of convergence (see Figure A1 for illustrations specific to the students included in the two-wave panel).
Table 1
Attitude distribution and means: A cross-sectional comparison across cohorts
 
Year 1
Year 2
Year 3
Year 1−Year 3
Mean
Std. D
Mean
Std. D
Mean
Std. D
Diff. Mean
Diff
Std. D
Refugees
2.72
1.14
2.82
1.14
2.89
1.15
0.17*
0.01
Women quotas
2.59
1.23
2.64
1.20
2.64
1.21
0.05
−0.02
Taxes
3.40
1.10
3.33
1.12
3.22
1.08
−0.18*
−0.02
Welfare dividends
2.76
1.17
2.97
1.26
3.09
1.18
0.33***
0.01
Note: *** p < 0.001; ** p < 0.01; * p < 0.05. N = 1753. The four different attitudes are assessed using a Likert scale, and the data represent the attitude distribution mean values across students in the first, second, or third year of their educational program (pooled data). The statistical significance is evaluated using independent t-tests. 1066 respondents answered in the first year, 476 in the second and 211 in the third
Fig. 1
Relationship between attitudes and years spent in education: Cross-sectional histograms. Note: N = 1753. The four different attitudes are assessed using a Likert scale, and the figure illustrates the attitude distribution across students in the first, second, or third year of their educational program. 1066 respondents answered in the first year, 476 in the second and 211 in the third
Full size image

Test 2

While the first test did not uncover systematic changes in attitude distribution over time, we proceed by asking if convergence may be found in different sub-groups in the student sample, based on their various social behaviors in class. Test 2 examines whether the attitudes of socially embedded individuals differ from less embedded individuals, concentrating on the absolute deviation between the individuals’ attitudes and the average attitude in their cohort.
Table 2 presents the estimated coefficients of social behavior on the deviation to the majority norm in one’s cohort on the different attitudes. It is striking that the degree of conformity appears unaffected by the social behaviors. No differences are found across the independent variables, apart from perceiving it being too many social activities in school for attitudes towards women quotas. These results differ from the model looking at absolute change without accounting for the average attitude in the cohort (Table A3), which curiously displayed significant correlations between social behaviors and attitude positions. However, when considering social norm adherence as in this case, individuals with a medium or high level of engagement do not significantly differ from those with low levels of engagement.9 The sample suffers from non-responses, explaining the slight decrease in sample size between test 1 and test 2.
Table 2
OLS regression: The association between social behavior and proximity to the cohort’s attitudinal mean
 
Refugees
Quotas
Taxes
Dividends
Social interactions
Low as ref
Medium engagement
−0.05
(0.06)
0.01
(0.06)
0.01
(0.06)
−0.01
(0.06)
High engagement
−0.06
(0.07)
0.03
(0.07)
−0.01
(0.06)
−0.2
(0.07)
Social experiences
Feeling anonymous
−0.01
(0.02)
−0.01
(0.01)
0.01
(0.01)
0.02
(0.02)
Difficult to make friends
0.01
(0.02)
−0.01
(0.02)
0.01
(0.01)
−0.01
(0.02)
Too many activities
0.02
(0.02)
0.03*
(0.01)
−0.01
(0.01)
0.01
(0.02)
Schools (KTH as ref)
SSE
0.01
(0.05)
0.03
(0.05)
0.03
(0.05)
0.04
(0.05)
GU
0.01
(0.05)
0.10
(0.05)
0.01
(0.05)
−0.02
(0.05)
Hanken
−0.14*
(0.06)
0.01
(0.06)
−0.11
(0.06)
−0.28***
(0.06)
Controls
YES
YES
YES
YES
Constant
0.99***
(0.15)
0.96***
(0.16)
0.66***
(0.15)
0.50***
(0.17)
R2
1.3%
1.3%
1.0%
3.5%
Observations
1368
1368
1368
1368
Note: *p < 0.05; **p < 0.01; ***p < 0.001. The models include clustered standard errors on ID in parentheses and fixed effects for schools and year. Age and gender are parts of the controls in these main models. The results are robust when including the parents’ education
Overall, the results from the OLS regression challenge conventional assumptions, as they suggest that there are no significant relationships between social behaviors and attitudinal conformism. Indeed, the explained variance of the models are poor: ranging from 1 percent for attitudes related to taxes to around 3 per cent for women quotas. The low level of explained variance is an indicator of socialization not being an important factor for explaining attitudes at this point in an individuals’s life trajectory: instead, it seems more likely that the closeness to the mean is the result of mere accident or background factors such as family socialisation. There are further no significant differences between the schools (with KTH as the reference category) except for two instances: Hanken shows a significant difference regarding welfare dividends (-0.28), which is expected since Finland, unlike Sweden, does not allow for welfare dividends. Additionally, Hanken is -0.14 more critical towards allowing refugees. As indirect contact with their peers might influence attitudes instead of the closer friend group (as noted by Mendelberg et al., 2017; Newcomb, 1943), the next stage of the analysis concentrates on exploring these associations looking at within-individual effects.

Test 3

We leverage the Covid-19 pandemic as an exogenous shock to test the causality of the socialization mechanism with a difference-in-difference design. The pandemic implied that the educational programs in Swedish and Finnish higher education were moved to being held online, largely closing campuses for more than a year with a start in mid-March 2020, as shown in Fig. 2.10 The treatment effectively exposes some students to more restricted social interactions while other students are unaffected. The treatment thus rests upon the assumption that the ‘Online cohort’ experienced less contact with their peers, and that the online programs/courses are less effective in socializing than the social interactions on campuses in normal circumstances.11
Fig. 2
Social restrictions on Swedish and Finnish business schools during the pandemic. Note: The calculation is based on the calendar year, counting from September to the beginning of June. The business schools in Sweden and Finland included in the sample held their education online from mid-March 2020. The ‘Campus cohort’ had approximately 72% of their first year on campus until the social restrictions were implemented
Full size image
The difference-in-difference model estimates the effect of having a reduced social network after one year of studies. The first difference thus compares the attitudes of the ‘campus cohort’ at t1 to those after one year of studies (t2). This cohort had the time and opportunity to develop social networks as usual. See figure A2 in the appendix for a model over the expected effect. The second comparison is between the ‘Online cohort’ at t1 to the attitudes after one year of studies on distance (t2). The cohort that started their bachelor program in 2020 spent significantly less time with their peers. Comparing the difference in attitudes for the cohorts is thus an estimation of the effect of having diminished social networks during studies in higher education on the formation of attitudes.12 A regression-focused equation that accounts for possible control variables and (clustered) standard errors would be formulated as follows:
$$Y_{it}=\alpha+\beta \text{Online}_{i}+\gamma \text{Time}_{t}+\delta_{DID} \text{Online}_{i} * \text{Time}_{t}+\rm{\theta Z}+e_{it}.$$
Yit is the distance to the attitude mean in the cohort for an individual in the period t, while α is the intercept. In turn, βOnlinei reflects whether the individual is treated or belongs to the control group and ranges between 0–1. γ Timet represents the pre- or post-treatment period. Subsequently, the following variable is an interaction term between them that takes the value 1 after one year of studies. The coefficient estimates the average treatment effect of interest. After that, the indicator Z of potential control variables and the error term are included in the equation.
Table 3 presents the estimates of the difference-in-difference model. Except the intercept, which represents the mean for the cohort studying on campus at the first point, none of the estimates are statistically significant. The school differences shows that there is some variation among the Swedish schools regarding attitudes towards quotas and taxes, the most significant disparity lies in Hanken’s stance on welfare dividends (−0.34***). Moreover, the explained variance remains consistently low across all models, suggesting that the analysis fails to substantially account for the observed variation in closeness to the cohort mean. It seems that the cohorts do not differ from each other, and there is no significant attitudinal change over time. Therefore, there is no systematic pattern of convergence in the data–as Fig. 3 further illustrates. In line with the reported findings, no significant differences are observed when looking at absolute change in attitudes (Table A4 and Figure A3), or when increasing the sample size by not restricting the sample to respondents that replied on all issues (Table A5).
Table 3
Difference-in-difference analysis: Closeness to cohort’s average attitude
 
Refugees
Quotas
Taxes
Dividends
Cohort
    
Online
−0.00
(0.10)
−0.12
(0.10)
0.11
(0.10)
−0.08
(0.10)
Time
0.04
(0.09)
−0.04
(0.08)
−0.06
(0.08)
0.01
(0.09)
Online: time
−0.01
(0.14)
0.15
(0.14)
−0.00
(0.14)
−0.05
(0.15)
School (KTH as ref.)
   
SSE
−0.01
0.10
0.17*
0.04
(0.08)
(0.08)
(0.07)
(0.08)
GU
0.06
0.22**
0.16*
0.02
(0.08)
(0.08)
(0.07)
(0.08)
Hanken
−0.15
−0.03
−0.14
−0.34***
(0.10)
(0.09)
(0.09)
(0.10)
R2
1%
1%
1%
1%
Intercept
1.03***
(0.06)
1.05***
(0.06)
0.88***
(0.06)
1.07***
(0.06)
N
375
375
375
375
Note: *** p < 0.001; ** p < 0.01; * p < 0.05. Fixed effects for schools are included in the models and clustered robust standard errors in parenthesis
Fig. 3
Difference-in-difference visualization: Lack of attitudinal convergence across cohorts. Note: The figure demonstrates the distance to the average attitudinal mean by cohort and time points from Table 3. There are no significant differences across cohorts or over time
Full size image

Limitations

The exposure to this treatment is considered random and unrelated to potentially important omitted variables. There might, however, be some spillover effects in the treatment, as Figure 2 illustrates. The 2019 cohort had one and a half semesters on campus until the first social distancing occurred. Even though the first semester is by far the most critical period to establish social connections (Tyllström et al., 2022), the cohort in 2019 experienced two and a half months of online education. Still, they were significantly more in contact with their social network than the treated cohort, as shown by the survey data and the fact that the education during the great majority of their first year was conducted on campus without any recommendations for social distancing.
However, the most obvious limitation of the design is the risk of violating the exclusion restriction assumption (Morgan and Winship, 2015). The trends in the dependent variable are not compared at simultaneous time points but during the student’s first- and second-year of studies. While the main intuitive implication of the time of the pandemic on students’ education is its severe effects on their social contacts and interactions, the pandemic may have impacted attitude development through other channels. For instance, the pandemic might lead to a change in attitudes due to personal experiences of the virus or through the increased presence of the state in people’s lives (Rosenfeld and Tomiyama, 2021).The pandemic is thus also a compound treatment. However, since the dependent variable is the difference between individuals’ attitudes and the norms in class, the risk with the treatment is reduced as convergence of attitudes is less of an obvious outcome. In addition, the research design of the difference-in-difference model could further be improved by empirically demonstrating that the parallel trend assumption holds before the treatment is implemented. Due to data availability, this is unfortunately not possible to assess. Still, there are no theoretical reasons to believe that the trends would differ between the cohorts before the treatment.

Concluding discussion

One of the core research areas in political science is understanding how citizens develop their political attitudes. This study contributes to the field by being among the first to directly test whether peer socialization fosters political attitudes within university cohorts. We leverage a unique dataset that tracks students from Swedish and Finnish top-ranked business schools and examine the link between their social behaviors and attitudes. The study further considers the political norms in their respective cohorts and thereby bridges the large literature in political science focused on directional attitudinal change from university attendance with a closer socialization perspective. Additionally, we leverage the Covid-19 pandemic as an exogenous shock that reduced the degree of contact between peers in certain cohorts, and thereby rely on both self-reported and objective measures of the students’ social interactions.
Contrary to the results of the study conducted in the U.S. by Mendelberg et al. (2017), but in line with the results by Strother et al. (2021), the findings did not support the idea of a general socialization mechanism within the university cohorts. There were no signs of convergence in attitudes over time, and we therefore do not have support for the first hypothesis, The second hypothesis was also rejected, as there were no significant differences between students who varied in their social behaviors. In fact, the models only explained a very limited part of the variability in attitudes, which suggests that background factors and earlier socialization are more important determinants for attitudes. While the design of the study did not allow us to make claims of the causality of attending university on attitude formation, suggestive results from the descriptive study largely aligned with the idea of education generating attitudinal change. Consequently, we underscore that if there indeed is a causal effect of attending university, the underlying mechanism is unlikely to be peer socialization.
These findings further contribute to our understanding of broader socialization processes, beyond a focus on the ‘higher-education effect’. The socialization effect may only apply to individuals from low socioeconomic backgrounds (see e.g., Lindgren et al., 2019), or to earlier stages in an individual’s life. Since the results diverge from the findings by Mendelberg et al. (2017), and considering that Strother et al. (2021) identified socialization effects only for roommates, the socialization may need to be even more intense or occur in smaller groups in order to hold a formative impact on students’ attitudes in this phase of a students’ educational journey.13 The effects of peer socialization may also be conditioned by the political environment through its impact on the saliency of political issues within the peer group (cf. Mendelberg et al., 2017). As such, there are higher levels of political polarization in the U.S, where both cited studies were fielded, which may increase the intensity and frequency of political discussions and thus the strength of the socialization. Furthermore, it is sometimes claimed that conflict avoidance is a characteristic of Nordic culture (cf. Daun & Helgesen, 2006) which might make students less prone to discuss sensitive political issues with each other. At any rate, inter-personal cultural differences have to our knowledge not been studied as a mediating factor in political socialization processes in educational institutions.
While students at elite business schools may be particularly likely to experience formative peer socialization (Schleef, 2005; Tyllström et al., 2022), the null result could also be attributed to the homogenous background of the students. These business students are predominantly from privileged family backgrounds, often more assertive than other student groups, and may possess strong pre-existing dispositions (Vedel & Thomsen, 2017). They could therefore be less susceptible to attitudinal change through peer interactions. Homophily in political values within close peer groups, as similar students are likely to be drawn to each other, may further cancel out any potential socialization effects (cf. McPherson et al., 2001), as would the fact that students who deviate from the political norms may interact less with their peers. While this possibility cannot fully be ruled out by this study, it would not explain the null result from the restrictions in social interactions imposed by the pandemic. Even if the study focused on business students, the data included different types of business schools in two different countries which might point to some of our findings being relevant also in other contexts. The fact that we find no consistent differences between schools also points to the fact that schools’ organization per se might have little to do with students’ values and homophily (similarly to the findings of Mayer & Puller, 2008). The most significant school difference–that Hanken differs on the issue of welfare dividends–is expected as Finland, unlike Sweden, already prohibits them.
One of the challenges of studies concentrating on peer socialization is to fully separate the possible effects of socialization from cognitive development resulting from the educational content. When students begin their studies in higher education, several processes coincide: they learn new things, develop skills, and become embedded in a new social context. To disentangle the mechanisms, one way forward could be to examine potential shocks to the school class composition, such as political reforms that increase school segregation or compare differences between students who stay on campus and those who commute. This study partially overcame these issues by leveraging data on students’ social behavior and political attitudes and concentrating on the cohorts’ attitude distribution. It thereby contributes both to the literature on the general ‘higher education effect’ as well as to the specifics of business education on students’ attitudes and values (Fischer et al., 2017; Miragaya et al., 2023). Naturally, this study calls for further research to test the results in different contexts and within more heterogeneous student groups in order to unequivocally challenge the peer socialization hypothesis. Nonetheless, this study reveals that the most prevailing mechanism to explain an ‘higher education effect’ is not as robust nor uniform as previously hypothesized.

Acknowledgements

The authors thank Mikael Persson and Johannes Lindvall as well as the three anonymous reviewers for their valuable feedback on earlier drafts of this paper. Additionally, the authors are grateful for the comments provided by Rune Stubager, Shane P. Singh, and the participants of the publication seminar at IPZ, Zürich, with a special mention to Reto Mitteregger. We also extend our thanks to Anna Tyllström and Gergei Farkas for their collaboration in collecting the survey data.

Declarations

Competing interests

The authors have no relevant financial or non-financial interests to disclose.

Ethics approval

This study has been approved by The Swedish Ethical Review Authority (ref. nos. 2018/648-31/5 and 2022–04279-02).
Informed consent was obtained from all individual participants included in the study.
Open Access This article is licensed under a Creative Commons Attribution 4.0 International License, which permits use, sharing, adaptation, distribution and reproduction in any medium or format, as long as you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons licence, and indicate if changes were made. The images or other third party material in this article are included in the article’s Creative Commons licence, unless indicated otherwise in a credit line to the material. If material is not included in the article’s Creative Commons licence and your intended use is not permitted by statutory regulation or exceeds the permitted use, you will need to obtain permission directly from the copyright holder. To view a copy of this licence, visit http://creativecommons.org/licenses/by/4.0/.

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Title
Does Peer Socialization Within Cohorts Foster Political Attitudes? A Longitudinal Study of Elite Business Students
Authors
Hilma Lindskog
Nils Gustafsson
Sofiya Voytiv
Publication date
28-10-2024
Publisher
Springer US
Published in
Political Behavior / Issue 2/2025
Print ISSN: 0190-9320
Electronic ISSN: 1573-6687
DOI
https://doi.org/10.1007/s11109-024-09978-y

Supplementary Information

Below is the link to the electronic supplementary material.
1
As Newcomb stated already over 80 years ago, 'Since values come to be values largely through the mediation of the groups with which an individual has contact, one cannot very sensibly study individuals’ values apart from groups’ (1943:84).
 
2
For instance, one of the schools in the study, SSE, implements RME through their Global Challenges courses, which "encourage self-reflection" and educate students about sustainability issues (https://www.hhs.se/globalchallenges).
 
3
Stockholm School of Economics (SSE); School of Business, Economics and Law at Gothenburg University (GU); the MSc in Industrial Management and Engineering at the Royal Institute of Technology (KTH), and Hanken School of Economics (Hanken).
 
4
The options ranges from ‘Very bad idea’ to ‘Very good idea’.
 
5
The issue of dividends concerns the relationship between the state and the market and has been debated in the region in recent years (Oscarsson and Holmberg, 2020).
 
6
Supplementary analyses using Swedish population data from the SOM Institute reveal that business students are more favorable toward reducing taxes, restricting refugee allowances, and prohibiting welfare dividends than the average Swedish population. Table A6 in the appendix provides further details.
 
7
The questions are introduced with the pre-text ‘To what extent have you experienced the following difficulties regarding social interaction among students at your school’. Thereafter follows: 1. Difficult to make friends among my fellow students, 2. I feel that the requirements for participation in various social contexts as part of student life are too high, 3. I feel anonymous due to the size of the student group.
 
8
Additional analyses using SOM Institute data among respondents aged 22 and 23 confirmed that age effects are unlikely to influence the differences in Table 1. The survey includes identical items on taxes, welfare dividends, and attitudes toward refugees in the span of 2017 and 2020. T-tests show that the small differences in means between the age groups are statistically insignificant. For taxes, the mean difference is 2.6 versus 2.8; for refugees, it is 3.5 for both groups; and for dividends, it is 2.4 versus 2.2.
 
9
Among the control variables, gender is significantly correlated with the dependent variables, with the strongest effect for the issue of women quotas (0.82*). Women are more different from the majority views in their cohort.
 
10
Finland had slighty more strict restrictions than Sweden.
 
11
The t-test further shows that on a continuous index over social behavior, the mean for the online cohort is 5.2 while it is 7.6 for the cohort studying at campus. The difference in mean is significant (p = 0.018), in line with the expectations of a reduced social life for the Covid cohort.
 
12
The pandemic did not cause an increase in dropouts among the students. The composition is also similar between the cohorts: the covid cohort had 38% women and the average social background was 2.67 on a four-scaled dimension. In comparison, the online cohort had 45% women and scored 2.58 on their average socio-economic background.
 
13
The First year of studies could be particularly influential. During this time, friendships are formed, and group identities take shape (Tyllström et al., 2022).
 
go back to reference Algan, Y., Dalvit, N., Do, Q., Le Chapelain & A., Zenou, Y. (2023). Friendship Networks and Political Opinions: A Natural Experiment among Future French Politicians (October 6, 2023). Available at SSRN: https://ssrn.com/abstract=4593953 or https://doi.org/10.2139/ssrn.4593953
go back to reference Anteby, M. (2013). Manufacturing morals: The values of silence in business school education. Chicago; London: University of Chicago Press.
go back to reference Apfeld, B., Coman, E., Gerring, J., & Jessee, S. (2022). Higher Education and Cultural Liberalism: Regression Discontinuity Evidence from Romania. The Journal of Politics,85(1), 34–48. https://doi.org/10.1086/720644CrossRef
go back to reference Bornschier, S., Häusermann, S., Zollinger, D., & Colombo, C. (2021). How “Us” and “Them” Relates to Voting Behaviour—Social Structure, Social Identities, and Electoral Choice. Comparative Political Studies,54(12), 2087–2122.CrossRef
go back to reference Boxell, G., & M., & Shapiro, J. M. (2022). Cross-Country Trends in Affective Polarization. The Review of Economics and Statistics,106(2), 557–565. https://doi.org/10.1162/rest_a_01160CrossRef
go back to reference Campbell, C., & Horowitz, J. (2016). Does College Influence Sociopolitical Attitudes? Sociology of Education,89(1), 40–58.CrossRef
go back to reference Cavaille, C., & Marshall, J. (2019). Education and Anti-Immigration Attitudes: Evidence from Compulsory Schooling Reforms across Western Europe. American Political Science Review,113(1), 254–263.CrossRef
go back to reference Daun, Å., & Helgesen, G. (2006). A Nordic Worldview. In Helgesen, G. and Risbjerg Thomsen, S. (eds) Politics, Culture and Self: East Asian and North European Attitudes, Copenhagen: NIAS Press.
go back to reference de Janasz, S. C., & Forret, M. L. (2008). Learning the art of networking: A critical skill for enhancing social capital and career success. Journal of Management Education,32(5), 629–650.
go back to reference d׳Hombres, B., & Nunziata, L. (2016). Wish you were here? Quasi-experimental evidence on the effect of education on self-reported attitude toward immigrants. European Economic Review,90, 201–224.CrossRef
go back to reference Dey, E. L. (1996). Undergraduate political attitudes: An examination of peer, faculty, and social influences. Research in Higher Education,37(5), 535–554.CrossRef
go back to reference Farrar, C., Green, D., Green, J., Nickerson, D., & Shewfelt, S. (2009). Does Discussion Group Composition Affect Policy Preferences? Results from Three Randomized Experiments. Political Psychology,30(4), 615–647.CrossRef
go back to reference Finseraas, H., Søraas Skorge, Ø., & Strøm, M. (2018). Does Education Affect Immigration Attitudes? Evidence from an Education Reform. Electoral Studies,55, 131–135.CrossRef
go back to reference Fischer, M., Kauder, B., Potrafke, N., & Ursprung, H. W. (2017). Support for free-market policies and reforms: Does the field of study influence students’ political attitudes? European Journal of Political Economy,48, 180–197.CrossRef
go back to reference Garritzmann, J. (2016). The Political Economy of Higher Education Finance. Springer International Publishing.CrossRef
go back to reference Gnambs, T., & Batinic, B. (2012). A Personality-Competence Model of Opinion Leadership. Psychology & Marketing,29(8), 606–621.CrossRef
go back to reference Gross, N., & Fosse, E. (2012). Why are professors liberal? Theory and Society,41(2), 127–168.CrossRef
go back to reference Haski-Leventhal, D., Pournader, M., & Leigh, J. (2022). Responsible Management Education as Socialisation: Business Students’ Values, Attitudes and Intentions. Journal of Business Ethics,176(1), 17–35.CrossRef
go back to reference Hjerm, E., & M. A., & Danell, R. (2018). Peer Attitudes and the Development of Prejudice in Adolescence. Socius : Sociological Research for a Dynamic World,4, 237802311876318. https://doi.org/10.1177/2378023118763187CrossRef
go back to reference Huckfeldt, R., & Sprague, J. (1991). Discussant Effects on Vote Choice: Intimacy, Structure, and Interdependence. The Journal of Politics,53(1), 122–158.CrossRef
go back to reference Kunst, S., Kuhn, T., & van de Werfhorst, H. (2020). Does education decrease Euroscepticism? A regression discontinuity design using compulsory schooling reforms in four European countries. European Union Politics,21(1), 24–42.CrossRef
go back to reference Lancee, B., & Sarrasin, O. (2015). Educated Preferences or Selection Effects? A Longitudinal Analysis of the Impact of Educational Attainment on Attitudes Towards Immigrants. European Sociological Review,31(4), 490–501.CrossRef
go back to reference Lindgren, K.-O., Oskarsson, S., & Persson, M. (2019). Enhancing Electoral Equality: Can Education Compensate for Family Background Differences in Voting Participation? American Political Science Review,113(1), 108–122.CrossRef
go back to reference Marshall, J. (2016). Education and Voting Conservative: Evidence from a Major Schooling Reform in Great Britain. The Journal of Politics,78(2), 382–395.CrossRef
go back to reference Mayer, A., & Puller, S. L. (2008). The old boy (and girl) network: Social network formation on university campuses, Journal of Public Economics, 92(1), 329–347. Available at:https://doi.org/10.1016/j.jpubeco.2007.09.001CrossRef
go back to reference Mengel, F. (2020). Gender differences in networking. The Economic Journal,130(630), 1842–1873.CrossRef
go back to reference McPherson, M., Smith-Lovin, L., & Cook, J. M. (2001). Birds of a Feather: Homophily in Social Networks. Annual Review of Sociology,27(1), 415–444.CrossRef
go back to reference Mendelberg, T., McCabe, K., & Thal, A. (2017). College Socialization and the Economic Views of Affluent Americans. American Journal of Political Science,61(3), 606–623.CrossRef
go back to reference Miragaya-Casillas, C., Aguayo-Estremera, R., & Ruiz-Villaverde, A. (2023). Self-selection or indoctrination in the study of (standard) economics: A systematic literature review. Theory and Research in Education,21(2), 176–196.CrossRef
go back to reference Morgan, Stephen L and Winship, Christopher. Counterfactuals and causal inference. Cambridge University Press, 2015
go back to reference Newcomb, T. M. (1943). Personality and social change: attitude formation in a student community (pp. 225). Dryden Press.
go back to reference Nickerson, D W. (2009). Experimental Approaches to the Diffusion of Norms. In Social Capital: Reaching Out, Reaching In, ed. Viva Ona Bartkus and James H. Davis. Northampton, MA: Edward Elgar, 186–204.
go back to reference Nie, N. H., Junn, J., & Stehlik-Barry, K. (1996). Education and Democratic Citizenship in America. University of Chicago Press.
go back to reference Oscarsson, H. & Holmberg, S. (2020). Swedish Voting Behavior. Swedish National Election Studies, Working Paper Series. Report 2020:1. University of Gothenburg, Department of Political Science.
go back to reference Paterson, L. (2009). Civic Values and the Subject Matter of Educational Courses. Oxford Review of Education,35(1), 81–98.CrossRef
go back to reference Persson, M. (2015). Education and Political Participation. British Journal of Political Science,45(3), 689–703.CrossRef
go back to reference Ricart-Huguet, J., & Paluck, E. L. (2023). When the Sorting Hat Sorts Randomly: A Natural Experiment on Culture. Quarterly Journal of Political Science,18(1), 39–73.CrossRef
go back to reference Rivera, L. (2016). Pedigree: How elite students get elite jobs. Princeton.
go back to reference Rekker, K., & L., Branje, S., & Meeus, W. (2017). The dynamics of political identity and issue attitudes in adolescence and early adulthood. Electoral Studies,46, 101–111. https://doi.org/10.1016/j.electstud.2017.02.005CrossRef
go back to reference Rosenfeld, D. L. & Tomiyama, A. J. (2021). Can a pandemic make people more socially conservative? Political ideology, gender roles, and the case of COVID-19. Journal of Applied Social Psychology,51(4), 425–433. https://doi.org/10.1111/jasp.12745CrossRef
go back to reference Sagiv, L., & Schwartz, S. (2000). Value priorities and subjective well-being: Direct relations and congruity effects. European Journal of Social Psychology,30(2), 177–198.CrossRef
go back to reference Schein, E. (1967). Attitude Change During Management Education. Administrative Science Quarterly,11(4), 601–628.CrossRef
go back to reference Schleef, D. J. (2005). Managing elites: Socializaton in law and business schools. Rowman & Littlefield Publishers.
go back to reference Scott, R. (2022). Does University Make You More Liberal? Estimating the Within-individual Effects of Higher Education on Political Values. Electoral Studies,77, 102471.CrossRef
go back to reference Simon, E. (2022). Demystifying the Link between Higher Education and Liberal Values: A Within-sibship Analysis of British Individuals’ Attitudes from 1994–2020. The British Journal of Sociology.,73(5), 967–984.CrossRef
go back to reference Strother L., Piston, S., Golberstein, E., Gollust, S. E., Eisenberg, D. (2021). College roommates have a modest but significant influence on each others political ideology. Proceedings of the National Academy of Sciences PNAS. https://doi.org/10.1073/PNAS.2015514117
go back to reference Stubager, R. (2008). Education Effects on Authoritarian-libertarian Values: A Question of Socialisation. The British Journal of Sociology. 59(2): 327–50.CrossRef
go back to reference Surridge, P. (2016). Education and Liberalism: Pursuing the Link. Oxford Review of Education,42(2), 146–164.CrossRef
go back to reference Tajfel, H. & Turner, J. C. (1986). The Social Identity Theory of Intergroup Behavior in Worchel, S. & Austin, W. G. (eds.) Psychology of intergroup relations. Chicago: Nelson-Hall.
go back to reference Terenzini, P. & Pascarella, E. (1991). Twenty Years of Research on College Students: Lessons for Future Research. Research in Higher Education,32(1), 83–92. https://doi.org/10.1007/BF00992835CrossRef
go back to reference Tyllström, A., Gustafsson, N., & Farkas, G. (2022). Becoming a business student: Negotiating identity and social contacts during the first three months of an elite business education. (pp. 1–23). (Institute for Futures Studies Working Paper; Vol. 2022, No. 13). Institute for Futures Studies.
go back to reference Van Zanten, A. (2009). The sociology of elite education. In The Routledge international handbook of the sociology of education (pp. 329–339). Routledge.
go back to reference Vedel, A., & Thomsen, D. K. (2017). The Dark Triad across academic majors. Personality and Individual Differences,116, 86–91.CrossRef
go back to reference Weinschenk, D., & C. T., & Oskarsson, S. (2021). Does Education Instill Civic Duty? Evidence from Monozygotic Twins in the United States and Sweden. International Journal of Public Opinion Research,33(1), 183–195. https://doi.org/10.1093/ijpor/edaa006CrossRef
go back to reference Westholm, A. (1999). The Perceptual Pathway: Tracing the Mechanisms of Political Value Transfer across Generations. Political Psychology,20(3), 525–551.CrossRef
go back to reference Woehler, M. L., Cullen-Lester, K. L., Porter, C. M., & Frear, K. A. (2021). Whether, How, and Why Networks Influence Men’s and Women’s Career Success: Review and Research Agenda. Journal of Management,47(1), 207–236.CrossRef
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