Ambivalent Sexism

Modern scholarly understandings of prejudice are typically grounded in Allport's (Reference Allport1954, 9) canonical definition of ethnic prejudice as ‘an antipathy based upon a faulty and inflexible generalisation’. While ethnic prejudice may be uniformly hostile, gendered prejudice is not (Winter Reference Winter2018). As Burns and Gallagher (Reference Burns and Gallagher2010, 430) observe, unlike racial inequalities, which are often entrenched by segregation, gender inequality involves ‘role segregation mixed with intimacy…. Gender is a hierarchy we often perpetuate in our families, with people we love.’ This feature of gender relations means that sexism – or sex-based prejudice – can encompass both antipathy and subjectively positive views that nevertheless perpetuate inequality.

To reveal the multidimensional nature of sexism, psychologists Glick and Fiske (Reference Glick and Fiske1996, 491) designed the ASI, a 22-item test that measures both hostile and benevolent sexism. Hostile sexism is an attitude that conforms to Allport's (Reference Allport1954) definition and involves ‘antipathy toward women who are viewed as usurping men's power’ (Glick and Fiske Reference Glick and Fiske2001, 109). It is measured on the ASI with items such as ‘Women seek to gain power by getting control over men’ (Glick and Fiske Reference Glick and Fiske1996, 512). Benevolent sexism refers to subjectively positive but ultimately disempowering beliefs about women and is characterised by a reverence for women in the roles of wives, mothers and romantic love objects (Glick and Fiske Reference Glick and Fiske1996). It is measured by statements such as ‘Women should be cherished and protected by men’ (Glick and Fiske Reference Glick and Fiske1996, 512). Although the word ‘benevolent’ has positive connotations, Glick and Fiske (Reference Glick and Fiske1996) make clear that benevolent sexism should be understood as conveying a combination of dominance and paternalism. There are three components to benevolent sexism: protective paternalism, whereby women are dependent on men as protectors and providers; complementary gender differentiation, reflecting a belief that women and their traits complement and complete men; and heterosexual intimacy, referring to men's desire for sexual and psychological closeness with women. As Glick and Fiske (Reference Glick and Fiske1996, 492) observe, both hostile and benevolent sexism view women as ‘the “weaker” sex … and … serve to justify men's structural power’. For a discussion of how the ASI compares to other measures of gender attitudes, see the Online Supplementary Material.

Who Is Sexist?

Glick and Fiske's (Reference Glick and Fiske1996) initial research showed that men score higher on the ASI than women, particularly for hostile sexism. In a subsequent cross-national study, Glick et al. (Reference Glick2000) found that, relative to men, women disavow hostile sexism but often endorse benevolent sexism. The authors observed that this tendency was strongest in sexist cultures, where women may potentially need the protection and idealisation associated with benevolent sexism in order to avoid hostility. In contrast, in egalitarian societies, women may reject benevolent sexism because they are less dependent on men and unlikely to incur sexist hostility if they refuse to adhere to conventional gender roles. Since Britain is relatively egalitarian, we expect women to have lower scores for both hostile and benevolent sexism than men.

Other studies suggest that education and age are associated with sexism. Those with lower levels of education tend to score high on hostile and benevolent sexism scales (Glick, Lameiras and Castro Reference Glick, Lameiras and Castro2002; Schaffner, Macwilliams and Nteta Reference Schaffner, Macwilliams and Nteta2018). Hellmer, Stenson and Jylhä (Reference Hellmer, Stenson and Jylhä2018) hypothesised that this could be due to exposure to discussions about sexism and gender inequality at universities and workplaces that require higher education. However, it could also be that less sexist individuals are more likely to pursue higher education or that unmeasured variables such as class explain the relationship.

The relationship between sexism and age is inconsistent, though the evidence broadly suggests older people are more sexist than younger people. Glick, Lameiras and Castro (Reference Glick, Lameiras and Castro2002) found that age was associated with more benevolent, but not hostile, sexism and suggest that this could be explained by preferences for maintaining the status quo increasing with age or by cohort differences. By contrast, Gaunt (Reference Gaunt2012) found that age had a weak and inconsistent effect, with older men and women being less likely to express hostile sexist beliefs but older women being more likely to endorse benevolent sexism. Garaigordobil and Aliri (Reference Garaigordobil and Aliri2013) observe that sexism increases with age, but not in a linear fashion. The authors found that respondents aged 14–18 had high ambivalent sexism scores that then decreased until the age of 54 before increasing again, and they speculated that young people initially adopt sexist attitudes partially because of behaviour modelled in video games and pornography (Garaigordobil and Aliri Reference Garaigordobil and Aliri2013).

Research has established a relationship between benevolent sexism and religiosity (Burns and Busso Reference Burn and Busso2005). Burns and Busso (Reference Burn and Busso2005) point to the benevolent justification of men's greater power and status compared to women in many religions: religious fundamentalisms express respect for the family and child rearing, and Bible passages evoke protective paternalism. Glick, Lameiras and Castro (Reference Glick, Lameiras and Castro2002) similarly found that Catholic religiosity predicted benevolent, but not hostile, sexism and suggested that the modern Catholic Church justifies conventional gender roles through the promotion of benevolent sexism, such as male priests assuming responsibility for the care and protection of the Church.

Studies have found correlations between authoritarianism and ambivalent sexism. Right-wing authoritarianism, often measured by the Right-Wing Authoritarianism (RWA) scale, encompasses three dimensions: (1) authoritarian submission/conservatism, prioritising respect for authority, social order and defence of the status quo; (2) authoritarian aggression/authoritarianism, a motivation to punish those who transgress established societal norms and conventions; and (3) conventionalism/traditionalism, including respect for traditional norms and values (Altemeyer Reference Altemeyer1981; Duckitt et al. Reference Duckitt2010). Holding an authoritarian world view should correlate with both hostile and benevolent sexism. Hostile sexism encompasses resentment against women who challenge patriarchal structures and norms, and should thus appeal to authoritarians who want to coercively maintain social structures. Benevolent sexism includes an adherence to traditional ideas of gender complementarity, male dominance and female fragility, and should therefore attract authoritarians who are motivated to uphold traditional values and ways of life. While some empirical research has found authoritarianism, measured using RWA, to be primarily associated with benevolent sexism (Christopher and Mull Reference Christopher and Mull2006; Sibley, Wilson and Duckitt Reference Sibley, Wilson and Duckitt2007), others have also found a strong positive relationship between RWA and hostile sexism (Austin and Jackson Reference Austin and Jackson2019; Hellmer, Stenson and Jylhä Reference Hellmer, Stenson and Jylhä2018).

This leads to our first hypothesis:

Sexism and Political Attitudes and Behaviours

Understanding sexism, and antipathy towards women specifically, is important because hostile sexism has been shown to influence political attitudes and behaviour. Cassese and Barnes (Reference Cassese and Barnes2019, 692), drawing on two hostile sexism items included in the American National Election Study, found that white women who endorse hostile sexism were more likely to support Trump in 2016, even after ‘controlling for education, ideology, partisanship, core values, racial resentment, and authoritarianism’. The authors observe that sexism and denying discrimination against women were strong predictors of white women's vote in 2016 but not of Romney support in 2012; this may be due to the salience of sexism in the 2016 campaign, having been generated by Clinton's historic candidacy and Trump's anti-woman behaviour and remarks. Cassese and Barnes (Reference Cassese and Barnes2019) suggest that white women might endorse sexist beliefs and power arrangements in order to protect the privileged status of white men, on whom they may be economically dependent, and thereby maintain their higher status vis-à-vis minority ethnic women. Schaffner, Macwilliams and Nteta (Reference Schaffner, Macwilliams and Nteta2018) similarly used four hostile sexism indicators in the nationally representative Cooperative Congressional Election Study and found that moving from the least to the most sexist end of the scale was associated with a 20-point increase in Trump support. Like Cassese and Barnes (Reference Cassese and Barnes2019), Schaffner, Macwilliams and Nteta (Reference Schaffner, Macwilliams and Nteta2018) note that the effects of hostile sexism were more potent in 2016 than 2012.

While hostile sexism has been shown to be predictive of Trump support, the relationship between benevolent sexism and voting behaviour is less clear. Bock, Byrd-Craven and Burkley's (Reference Bock, Byrd-Craven and Burkley2017) study of undergraduate students examined hostile and benevolent attitudes and found that only the former predicted Trump support. The authors observe that benevolent sexism rewards women who adhere to conventional gender roles, while hostile sexism punishes women who deviate from traditional norms; as an agentic woman seeking a leadership position, Clinton ‘represented the quintessential backlash candidate’ (Bock, Byrd-Craven and Burkley Reference Bock, Byrd-Craven and Burkley2017, 192). Ratliff et al. Reference Ratliff2017 study, administered to Project Implicit volunteer respondents, similarly concluded that hostile, but not benevolent, sexism predicted Trump support, controlling for political ideology, gender and attitudes towards minorities. Ratliff et al. Reference Ratliff2017 speculate that hostile sexism could be associated with negative attitudes towards Clinton because of her disruption of the status quo in seeking a leadership role, as well as positive attitudes towards Trump due to his offensive statements directed at women.

However, drawing on nationally representative survey data, Winter (Reference Winter2018) found that voters high in hostile and benevolent sexism were more likely to support Trump over Clinton, yet benevolent sexism was irrelevant for voter choice at the congressional level. To understand this result, Winter (Reference Winter2018) conducted a conjoint experiment where candidate sex and gendered style (for example, collaborative and cooperative or decisive and forceful) were randomly assigned. This experiment revealed that benevolent sexists opposed candidates with feminine styles and supported candidates with masculine styles, regardless of the candidate's sex. Winter (Reference Winter2018) concludes that hostile sexists are resistant to female leadership, while benevolent sexists reject symbolically feminine leadership and may be particularly sensitive to role congruity.

The studies discussed earlier were all conducted in the United States, where questions of gender ideology are, and have historically been, particularly salient (Campbell Reference Campbell2016). The theoretical link between sexism and electoral choice is also sometimes unclear. Many studies conclude that there was something particular about the 2016 presidential election: the first female presidential nominee from a major party (Clinton) as opposed to an openly sexist male candidate (Trump). Schaffner (Reference Schaffner2022) finds a strengthened relationship between hostile sexism and vote choice in the 2018 midterms, but this also cannot be separated from the Trump presidency. An alternative explanation is that sexists prefer conservative candidates in general, rather than Trump in particular, because they are seen as upholding traditional gender roles. Conversely, non-sexists might prefer left-wing candidates because they are more likely to emphasise women's rights. The literature therefore presents a convincing case that hostile – and perhaps benevolent – sexism was associated with Trump support in 2016, but more research is needed to test whether similar associations hold in other contexts.

Furthermore, the existing research contains methodological and measurement limitations. With the exception of Winter (Reference Winter2018), none of these studies use a nationally representative sample to measure both hostile and benevolent sexism. Studies that do draw on nationally representative samples only measure hostile sexism (Cassese and Barnes Reference Cassese and Barnes2019; Schaffner, Macwilliams and Nteta Reference Schaffner, Macwilliams and Nteta2018), whereas other studies that examine both hostile and benevolent sexism draw on university students and volunteers (Bock, Byrd-Craven and Burkley Reference Bock, Byrd-Craven and Burkley2017; Ratliff et al. Reference Ratliff2017). It is unclear, therefore, whether the benevolent sexism findings will hold in a representative sample. We thus need to investigate sexism and its association with political attitudes and behaviour in other environments using nationally representative survey data. Britain provides an excellent context, as gender has tended to be less politically salient than in the United States but comparisons have been made between Trump's election and the success of the Leave side in the 2016 EU referendum (see, for example, Inglehart and Norris Reference Inglehart and Norris2017).

We anticipate that sexists should be more likely to have voted Leave in the EU referendum. In the context of US politics, Deckman and Cassese (Reference Deckman and Cassese2019, 6) use the idea of gendered nationalism – that is, the belief that the United States has grown ‘too soft and feminine’ – to argue that gendered beliefs exert an important influence on political behaviour. They found that voters who endorse gendered nationalism were more likely to support Trump, possibly because the overt masculinity of his campaign resonated among those who were concerned that the nation was becoming too weak. Brexit rhetoric arguably contained similarly masculine appeals, with such key Leave campaigners as Boris Johnson (Reference Johnson2016) claiming that ‘the public can see all too plainly the impotence of their own elected politicians’ in the face of EU regulation and Michael Gove (Reference Gove2016) asserting that ‘Britain would be stronger outside of the EU’, while rhetorically asking ‘are we really too small, too weak and too powerless to make a success of self-rule?’. That the idea of control formed a key part of the Brexit campaign – as evidenced by its slogan ‘Take Back Control’ – is also notable given that the gender studies literature indicates that exerting control is a key feature of masculinity (Schrock and Schwalbe Reference Schrock and Schwalbe2009). It is therefore possible that Leave campaign language propagated a masculine-coded view of both Brexit and the state, thus issuing a latent appeal to sexist voters. Additionally, Green and Shorrocks (Reference Green and Shorrocks2021) found that men who perceived men to be discriminated against were more likely to vote Leave, even after controlling for sociodemographic characteristics and values.

We also expect sexists to be more likely to have voted Conservative in the 2019 general election. This is both because of the strong connection between voting Leave in 2016 and voting Conservative in 2019 (Prosser Reference Prosser2020), and the expectation that those who hold sexist attitudes might vote for conservative candidates and parties because of their association with traditional hierarchies and lifestyles. Additionally, research suggests that voters may ascribe a masculine or feminine gender identity to political parties. Winter's (Reference Winter2010) study found that US voters were more likely to associate stereotypically masculine traits, such as strength and self-confidence, with the Republican Party, and stereotypically feminine traits, such as kindness and care, with the Democratic Party. These associations may arise because of party ‘ownership’ of certain issues (whereby Republicans are viewed as better at handling defence and crime, and Democrats are seen as stronger on education and healthcare) and the relative visibility of women within the Democratic Party (Winter Reference Winter2010). Within Britain, similar dynamics are at play: over 50 per cent of Labour Party MPs are women, and voters view the party as better able to handle healthcare, whereas the Conservatives are seen as more competent on defence and security (YouGov 2019). These perceptions might lead sexists to disdain the Labour Party and support the Conservatives.

Although the association between benevolent sexism and political behaviour has been less strong in some work (Bock, Byrd-Craven and Burkley Reference Bock, Byrd-Craven and Burkley2017; Ratliff et al. Reference Ratliff2017), Winter's (Reference Winter2018) use of the ASI in a nationally representative survey found an association between both hostile and benevolent sexism and Trump support; as such, we hypothesise that both hostile and benevolent sexism will be associated with Leave/Conservative voting. It is important to note that although we expect to find associations between sexism and Leave and Conservative voting, we are not attempting to demonstrate causal relationships.Footnote ¹ However, we do expect these relationships to hold, even after controlling for confounding factors, such as age, education and political values. Therefore, our remaining hypotheses are:

Data

We embedded ambivalent sexism questions in two surveys. The first survey was fielded to 1,611 respondents just prior to the UK general election in December 2019, with funding from the Elections, Public Opinion and Parties (EPOP) section of the Political Studies Association, and is hereafter referred to as the EPOP survey. The second survey is the British Elections Study Internet Panel (BESIP) (Fieldhouse et al. Reference Fieldhouse2020). Our questions were part of Wave 19, conducted in January 2020, just after the election. Approximately 8,000 BESIP respondents completed the ambivalent sexism module, though much of our analysis is conducted on a subset of these respondents due to missing values on other variables. Both surveys were conducted online by YouGov and were weighted to be representative of the British adult population on key demographics. Conducting two surveys using the ambivalent sexism items is a valuable contribution. As these questions have not been fielded to nationally representative samples in Britain before, our approach allows us to test the sensitivity of the scales and consistency of results across different samples, scale constructions and response categories. This is important, as political scientists increasingly use the ASI to understand political behaviour and attitudes.

We included four ambivalent sexism items in the EPOP survey and six items in the BESIP (see Table 1). Due to space and time constraints in these surveys, it was not possible to run the full 22-item ASI. The items were selected because they are comparable to those included in US studies of sexism and political behaviour that use a subset of these items (Cassese and Barnes Reference Cassese and Barnes2019; Cassese and Holman Reference Cassese and Holman2019; Frasure-Yokley Reference Frasure-Yokley2018; Schaffner, Macwilliams and Nteta Reference Schaffner, Macwilliams and Nteta2018). When it comes to hostile sexism, these are three out of the six items that contribute the most to the latent concept, and the correlation between these items and the full 22-item scale is very strong (Schaffner Reference Schaffner2021), suggesting that we do not lose much by restricting the items we use. To our knowledge, a similar study investigating reduced surveys for benevolent sexism is not available, and so we are more reliant here on our own judgement of which items are particularly representative of the concept and the items that have been used in studies in the United States. We discuss the measurement of benevolent sexism in our conclusion.

Table 1.

Ambivalent sexism items included in EPOP and BESIP surveys

In both surveys, respondents could agree or disagree with the statements using a five-point scale that ranged from ‘agree strongly’ to ‘disagree strongly’, with a midpoint of ‘neither agree nor disagree’. In the BESIP, respondents had a ‘don't know’ option. We provide an overview of the percentage of ‘don't know’ responses to the BESIP items in the Online Supplementary Material. Most items received less than 5 per cent of ‘don't know’ responses, but 9 per cent of respondents chose ‘don't know’ for the benevolent sexism ‘purity’ item. For the remainder of the analyses, we exclude the ‘don't know’ responses from the BESIP data.

Due to space considerations, the analyses that follow mostly use the BESIP data, which include more demographic and attitudinal variables than the EPOP data and hence allow us to present more complete models of political behaviour. We replicate our analysis using the EPOP data in the Online Supplementary Materials and discuss any relevant differences between the two data sets in the text.

Hostile and Benevolent Sexism Scales

We first examined the correlations between the hostile and benevolent sexism items. Using the BESIP data, we find that the Cronbach's alpha is 0.77 for the hostile items and 0.67 for the benevolent items. This was 0.71 and 0.52, respectively, in the EPOP survey, which only used two items each for hostile and benevolent sexism. Glick and Fiske (Reference Glick and Fiske1996; Glick and Fiske Reference Glick and Fiske2001) previously noted the higher internal consistency of the hostile sexism index in comparison to the benevolent sexism index and suggest that this reflects the multidimensionality of benevolent sexism (see earlier). We cannot comprehensively address this multidimensionality with our limited question items that capture only two out of the three dimensions (protective paternalism and complementary gender differentiation). However, our lower consistency scores for benevolent sexism are in line with what would be expected for this index.

All six items combined have a Cronbach's alpha of 0.83, but we analyse hostile and benevolent sexism separately. The two dimensions of sexism are conceptually different. Moreover, they have been found to load onto two factors (Glick and Fiske Reference Glick and Fiske1996; Glick and Fiske Reference Glick and Fiske1997; Schaffner Reference Schaffner2021), which we replicated in both surveys through exploratory factor analysis. The correlation between the separate hostile and benevolent sexism scales (0.36) is also not high. To create hostile and benevolent scales, we simply sum a respondent's answers across all three items. The scales have been coded to range from −1 to + 1 on a continuous scale, where negative values indicate disagreement with the statement (low sexism levels) and positive values indicate agreement with the statement (high sexism levels).

In the following analysis, we describe the extent of the British population's hostile and benevolent sexist attitudes; investigate these attitudes’ key predictors; and analyse the extent of sexism's association with EU referendum and 2019 general election vote choices.

Does the British Electorate Hold Sexist Attitudes?

Figure 1 shows the distribution of the hostile and benevolent sexism scales in the BESIP. Positive values reflect higher levels of sexism. Both the hostile and benevolent distributions are left-skewed towards the non-sexist end of the scale and peak at the midpoint (0) of the scales, with approximately 20 per cent of respondents at this midpoint. Approximately 30 per cent of respondents fall on the sexist end of the hostile sexism scale and 35 per cent of respondents fall on the sexist end of the benevolent sexism scale. The Online Supplementary Materials provide these distributions for the EPOP survey, where the proportion of respondents at the midpoint is somewhat higher: 25 per cent for the hostile scale and 30 per cent for the benevolent scale. In the EPOP data, we find a similar percentage of respondents at the sexist end of the benevolent scale (35 per cent) but a much higher percentage on the sexist end of the hostile scale (42 per cent).

Fig. 1.

Distributions of hostile and benevolent sexism in BESIP.

Notes: N = 7,752 for hostile sexism and N = 7,799 for benevolent sexism. Data are weighted.

This difference could be related to the absence of a ‘don't know’ option in the EPOP survey and explain the higher proportion of respondents who opted for the midpoint in this survey. It could also be the case that a ‘don't know’ option is perceived as a more socially desirable answer to someone who would otherwise answer at the sexist end of the scale, thereby reducing the prevalence of sexism in the BESIP data. This could especially be the case for hostile sexism. The level of sexism we find for our British samples is lower than that found in the United States, where Edwards and Schaffner (Reference Edwards and Schaffner2020) find that nearly half of American respondents in 2019 were on the hostile end of the scale, and around 60 per cent fell on the benevolent end of the scale.

We further examine the percentage of respondents that are sexist on both scales and which percentage hold exclusively hostile (but not benevolent) attitudes, and vice versa. To do so, we divide the sample into three categories: those who score a total of 0 (the midpoint) are considered ‘neutral’; those who scored above 0 are considered sexist on the particular indicator (hostile or benevolent); and those who score below 0 are considered non-sexist on that indicator.

The percentages of respondents in each category are shown in Table 2. A total of 26 per cent of respondents are not sexist on either indicator. This non-sexist group is majority female (65 per cent), Labour voting (47 per cent) and Remain voting (69 per cent); the mean age of this group is 46. A total of 17 per cent of respondents are sexist on both the hostile and benevolent scales.Footnote ² This group is majority male (64 per cent), Conservative voting (57 per cent) and Leave voting (70 per cent); the mean age of this group is 50. More than half the sample (53 per cent) holds sexist attitudes in some way or another – either hostile or benevolent, or both. A total of 12 per cent hold hostile but not benevolent views, whereas 11 per cent hold benevolent but not hostile views.

Table 2.

Intersection of hostile and benevolent sexist attitudes in UK

Notes: Data are weighted. N = 7,714.

The results are broadly the same in the EPOP data, with a slightly higher proportion again holding either or both types of sexist attitudes (60 per cent). We conclude that sexist attitudes are prevalent among the British population. In both surveys, more than half of respondents hold some sexist attitudes and almost 20 per cent hold both hostile and benevolent sexist attitudes.

We now look at the mean difference in sexism scores for the entire sample, as well as for key groups: men v. women, Labour v. Conservative voters and Leave v. Remain voters. The differences are calculated using bivariate ordinary least squares (OLS) regressions, and the coefficients in Table 3 show the difference in the mean sexism scores between the various groups. We find that women are significantly less likely to hold hostile sexist attitudes than men and that Conservative voters and Leave voters are significantly more likely to hold hostile sexist attitudes than Labour voters and Remain voters. We also find statistically significant gaps between political groupings for benevolent sexism, though they are much smaller in magnitude. The EPOP data show the same patterns, except the difference between men and women on the benevolent indicator is not statistically significant.

Table 3.

Sexist attitudes by gender and political grouping

Notes: Estimates are obtained using bivariate OLS regression models with survey weights. Coefficients represent the difference in means between the various groups (men/women, Conservative/Labour and Leave/Remain). Sexism scales range from −1 to +1. Standard errors are in parentheses. *** p < 0.001; ** p < 0.01; * p < 0.05.

In both surveys, we find that the size of the gap between men and women is substantively smaller than the gap between Conservative and Labour voters and the gap between Leave and Remain voters. This accords with US research, which finds that divisions in sexist attitudes are more likely to be found along political rather than gender lines (Ratliff et al. Reference Ratliff2017). There is more agreement about sexism between men and women than there is between Conservative and Labour voters and between Leave and Remain supporters in Britain.

What Predicts Sexist Attitudes in the British Electorate?

We now investigate the sociodemographic and attitudinal variables associated with sexism in Britain. H1 expected that male, older, less educated, more religious and more authoritarian people would score higher on the sexism scales. To test this, we first run OLS regression models with the hostile and benevolent sexism scales as dependent variables. Our key predictors include gender, age, education and religion, with additional controls for occupational class, employment status and marital status. We then run a second model where we add libertarian–authoritarian values as well as the left–right ideological placement scales. With regards to measuring authoritarianism, there is no RWA scale in the BESIP. However, the authoritarian–libertarian scale we used includes items that are very similar to some of the RWA items, especially those used in reduced RWA scales (see, for example, Bizumic and Duckitt Reference Bizumic and Duckitt2018), and tap into the three facets of authoritarianism described earlier. For example, the authoritarian–libertarian scale includes items such as: ‘Young people today don't have enough respect for traditional British values’ (measuring traditionalism); ‘People who break the law should be given stiffer sentences’ (measuring authoritarianism); and ‘Schools should teach children to obey authority’ (measuring conservatism). This authoritarian–libertarian scale is also used extensively in studies of British political behaviour and has become increasingly predictive of this behaviour in recent years (Fieldhouse et al. Reference Fieldhouse2019).

Figures 2a and 2b plot the coefficients from the multivariate models for the BESIP. We find clear and consistent results for gender, religion, education and political values. As expected, women score lower for both hostile and benevolent sexism, even after controlling for sociodemographic and attitudinal variables. We replicate this finding with the EPOP survey for hostile but not benevolent sexism, which suggests that gender differences might be more robust for the hostile indicator. We note however that in the EPOP data, we do not have the ability to control for religion, nor are we able to control for left–right position or authoritarianism (see Part B of the Online Supplementary Materials).

Fig. 2a.

Coefficient plots from OLS regression predicting hostile sexism (BESIP).

Notes: N = 3,096. Data are weighted, coefficients are unstandardised and 95 per cent confidence intervals are shown.

Fig. 2b.

Coefficient plots from OLS regression predicting benevolent sexism (BESIP).

Notes: N = 3,108. Data are weighted, coefficients are unstandardised and 95 per cent confidence intervals are shown.

When it comes to age, our descriptive results suggest that it is the 18- to 25-year-olds that are particularly non-sexist, especially for hostile sexism,Footnote ³ though this is no longer significant once we control for political values, suggesting that the differences are reflective of age-based value differences (Shorrocks Reference Shorrocks2018). In line with H1, there is a negative association between higher education and both hostile and benevolent sexism (also replicated in the EPOP survey). University-level education (undergraduate or postgraduate) is particularly significant. This educational gradient, however, disappears once we include left–right and authoritarian–libertarian values, suggesting that the educational divide is a value divide. We also find that those who identify as religious are more sexist (both hostile and benevolent) than those without a religion. This is true for both those who belong to the Church of England, Catholics and those belonging to another religion. The association between religiosity and sexism remains statistically significant once value indicators are included for benevolent, but not hostile, sexism, suggesting that for hostile sexism, some of the association between religion and sexism is mediated by values (see also Burn and Busso Reference Burn and Busso2005).

Authoritarianism is positively correlated with sexism. The relationship is of a similar magnitude for both hostile and benevolent sexism. This is in line with the theoretical expectation that sexist attitudes are held by authoritarians because of their desire to maintain traditional values and hierarchies, and to punish those who transgress them, and supports research that shows authoritarianism to be linked to both benevolent and hostile forms of sexism.

We do not find any clear patterns for control variables. Those in lower supervisory or technical occupations are more sexist than those in managerial or professional occupations, but this association disappears when values are controlled for. Those in routine or semi-routine professions are more likely to hold benevolent attitudes, even when controlling for political attitudes. Those who are unemployed score lower on benevolent sexism compared to those in full-time work, also controlling for values, but this is not replicated in the EPOP survey. In the BESIP survey, we further find that those that are cohabiting or are single exhibit lower levels of benevolent sexism than those who are married, but this does not hold when controlling for political values. In the EPOP survey, we find that those who are in a civil partnership are less likely to hold benevolent sexist attitudes compared to those who are married. Finally, those who are right-wing on the left–right value scale are more likely to endorse hostile sexism, while those who are more left-wing endorse benevolent sexism to a greater degree. These results are smaller in magnitude (0.01–0.02 points on a −1 to +1 scale), however, in comparison with the results for the libertarian–authoritarian scale (0.07 points).

In supplementary analysis, we find that gay, lesbian or bisexual respondents have statistically significantly lower scores for both hostile and benevolent sexism compared to those who identify as heterosexual, even when controlling for the attitudinal variables (see the model in the Online Supplementary Materials). This finding might reflect the more liberal ideological preferences held by lesbian, gay and bisexual people (Turnbull-Dugarte Reference Turnbull-Dugarte2020).

It should finally be noted that the US literature has identified considerable racial differences when it comes to sexism (Bracic, Israel-Trummel and Shortle Reference Bracic, Israel-Trummel and Shortle2019; Cassese and Barnes Reference Cassese and Barnes2019; Frasure-Yokley Reference Frasure-Yokley2018). We are unable to disaggregate by race and ethnicity due to the small sample sizes of black and minority ethnic respondents. Specifically, 86 per cent of our BESIP sample is White British and 5 per cent is Other White. Given this limitation, we suggest that our results should be interpreted as reflecting the attitudes of white British people, and indeed when we exclude the small number of black and minority ethnic respondents from the BESIP analysis, we get substantively similar results to those presented here.Footnote ⁴ Black and minority ethnic voters could be oversampled in future electoral surveys in Britain (see Frasure-Yokley Reference Frasure-Yokley2018) to remedy this deficiency in our analysis.

In conclusion, our most consistent findings are that: women particularly exhibit lower levels of hostile sexism; those with higher levels of education are less sexist; and religious individuals score higher on the (especially benevolent) sexism indicators. Authoritarians are more sexist, and controlling for both libertarian–authoritarian and left–right values renders the education (but not gender and religiosity) coefficients statistically insignificant.

Are Sexist Attitudes Associated with British Political Behaviour?

The 2016 EU Referendum

Next, we test the relationship between sexism and vote choice in the 2016 EU referendum (H2). We run two sets of logistic regression models predicting vote choice in the 2016 referendum, where the dependent variable is having voted Leave as opposed to Remain. The first model includes just the hostile and benevolent sexism scales, then we add controls for sociodemographics and political values. This includes several variables that were not included in the prediction of sexism models: attitudes towards immigrants; English identity; and a set of variables that measures respondents' attitudes towards equal opportunity efforts for women, gay people and black people.Footnote ⁵ These additional variables are included because xenophobic attitudes, racism, traditionalism and attitudes related to the maintenance of social order and hierarchy have been shown to be related either to voting Leave or to voting for traditional Conservative Party options, or to correlate with sexist attitudes (Christopher and Mull Reference Christopher and Mull2006; Deckman and Cassese Reference Deckman and Cassese2019; Evans and Mellon Reference Evans and Mellon2019; Fieldhouse et al. Reference Fieldhouse2019; Schaffner Reference Schaffner2021; Reference Schaffner2022 Schaffner, Macwilliams and Nteta Reference Schaffner, Macwilliams and Nteta2018; Sobolewska and Ford Reference Sobolewska and Ford2020).

To capture xenophobia, we use two measures of immigration attitudes. Respondents were presented with the statements ‘Immigration is good/bad for the economy’ and ‘Immigration enriches/undermines cultural life.’ Respondents could place themselves on a seven-point scale. To measure English identity, respondents were asked to place themselves on a seven-point scale based on their level of agreement with the statements. To capture traditionalism, racism and attitudes towards social hierarchy more generally – assuming that traditional social hierarchy is white, male and heterosexual – we used a set of questions where respondents were asked whether: ‘Attempts to give equal opportunities to (black people/women/gays and lesbians) have gone too far or not far enough.’ Respondents could answer on a five-point scale, ranging from ‘have not gone nearly far enough’ to ‘have gone much too far’.

Figure 3 shows the predicted probability of voting Leave by levels of hostile and benevolent sexism for these models (regression tables are available in the Online Supplementary Materials). The top row displays the predicted probability of voting Leave at various levels of hostile sexism, with the bottom row doing so for benevolent sexism. The first column provides graphs for the model that includes sexist attitudes only; in the second column, we add a set of demographic controls; and in the last column, we add the political attitudes.

Fig. 3.

Predicted likelihood voting Leave in the EU referendum at various levels of sexism (BESIP).

Notes: N = 2,433. Predicted probabilities calculated from a logistic regression model with other variables held at their means; 95 per cent confidence intervals shown.

Consistent with the descriptive associations, we find a positive and statistically significant association between both hostile and benevolent sexism and Leave voting. This association holds when we include demographic controlsFootnote ⁶ – but not when we control for political attitudes. In line with other research, we find strong associations between immigration attitudes, English identity and authoritarianism variables and voting Leave in the EU referendum. We find no significant associations with the equal opportunity variables. The descriptive association between sexism and voting Leave thus does not hold after controlling for other key predictors of Leave voting.

Since our dependent variable in the previous models was measured before our attitudinal variables, we also ran the models for vote intention in a hypothetical EU referendum, rather than referendum vote in 2016. Using this dependent variable produces similar results for benevolent sexism, but stronger results for hostile sexism: the association with voting Leave in a future hypothetical referendum and hostile sexism remains even when political attitudes are included, though it becomes substantively smaller. This may suggest that sexist attitudes have become a more important political dividing line since the referendum took place in 2016.

The 2019 general election

Next, we test whether sexist attitudes are associated with voting behaviour in the 2019 general election (H3). We run multinomial logistic regression models with the outcome options Conservative, Labour, Liberal Democrat and other; non-voters are excluded. In this section, we focus on support for the Conservatives only in comparison to Labour because these are the parties that the vast majority of voters in 2019 endorsed. Similar to the EU referendum models, we start with a simple bivariate model of sexist attitudes and 2019 vote, and then add control variables in a stepwise manner, first for sociodemographics and then adding values and EU referendum vote. Given the continued importance of the issue of Brexit and Leave and Remain identities (Hobolt, Leeper and Tilley Reference Hobolt, Leeper and Tilley2020; Sobolewska and Ford Reference Sobolewska and Ford2020), controlling for EU referendum vote is a conservative test of the relationship between sexism and vote choice because we expect EU referendum vote choice to be highly predictive of 2019 vote. The results are presented as predicted probabilities calculated from the models (shown in full in the online Supplementary Material) in Figures 4a and 4b.

Fig. 4a.

Predicted probability of voting Conservative and Labour by hostile sexism.

Notes: N = 2,295. Predicted probabilities calculated from a multinomial logistic regression model with other variables held at their means; 95 per cent confidence intervals shown.

Fig. 4b.

Predicted probability of voting Conservative and Labour by benevolent sexism.

Notes: N = 2,295. Predicted probabilities calculated from a multinomial logistic regression model with other variables held at their means; 95 per cent confidence intervals shown.

We find that there is a positive association between both hostile and benevolent sexism and voting Conservative when we do not control for additional attitudes. For hostile sexism, this association remains when we control for sociodemographic characteristics, political values and even EU referendum vote choice. The relationship is also strong, with a difference of 0.10 points in the predicted probability of voting Conservative between the lowest levels of hostile sexism and the highest. Although we cannot establish causality, it is notable that individuals who are otherwise similar in terms of sociodemographic features, authoritarianism, left–right values, immigration attitudes, nationalism, attitudes towards equal the opportunities of minorities and even EU referendum vote differed in their vote choice in 2019 depending on the extent to which they endorsed hostile sexist attitudes. This shows that even in a context where gender was not a particularly salient element of the election campaign, sexist attitudes are important in understanding electoral choice in Britain.Footnote ⁷

We do not, however, find a robust effect for a relationship between benevolent sexism and 2019 vote choice. The statistically significant relationship between benevolent sexism and vote choice remains after controlling for sociodemographics but not when controlling for political attitudes and EU referendum vote choice. H3 is thus partially supported: hostile, but not benevolent, sexism is associated with Conservative voting in 2019. We replicate our hostile sexism finding with the EPOP survey, but we do not find any significant associations between benevolent sexism and Conservative Party vote choice – even when excluding EU vote – when using the EPOP data.Footnote ⁸ This suggests that the association between hostile sexism and party choice is more stable than that between benevolent sexism and party choice.