This article delves into the dynamic landscape of attitudes toward homosexuality among secondary school students in Hong Kong, tracking changes over a decade from 2011 to 2021. The study employs multiple group latent class analysis to uncover complex patterns and shifts in public opinion, revealing a growing acceptance of homosexuality among adolescents. Key findings highlight the influence of gender, age, sexual orientation, and exposure to online sexual knowledge on attitudinal patterns. The research also explores the impact of cultural factors, such as Confucian values and Western Christian influences, on societal attitudes. Additionally, the article discusses the implications of these findings for policy and practice, emphasizing the need for continued progress in promoting inclusivity and addressing subtle forms of discrimination. The study's detailed examination of attitudinal dimensions and its use of advanced statistical methods provide a nuanced understanding of the evolving social landscape in Hong Kong.
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Abstract
Purpose
This study aims to investigate the heterogeneity in attitudes toward homosexuality among secondary school students in Hong Kong and examine whether and how the attitude patterns had shifted between 2011 and 2021. Factors that influenced the attitude patterns were also examined.
Methods
Three dimensions of attitudes toward homosexuality were measured: general attitudes, attitudes toward formal rights, and attitudes toward informal privileges. Latent class analysis and multiple group latent class analysis were employed to analyze data from a repeated cross-sectional survey conducted in 2011, 2016, and 2021, involving a total of 10,769 adolescents.
Results
In 2011, three attitude classes were identified: intolerant, neutral, and inclusive. However, both 2016 and 2021 revealed a four-class model, consisting of three classes similar to those observed in 2011, and a new “partially inclusive” class. The prevalence of these attitude classes had shifted over the study period. Sex, age, sexual orientation, and exposure to online sexual knowledge were associated with the attitude patterns.
Conclusion
A notable increase in the acceptance of homosexuality was observed among Hong Kong adolescents from 2011 to 2021. However, their attitudes toward different topics of homosexuality were not entirely consistent.
Policy implications
This study provides valuable insights for policymakers and practitioners in assessing the compatibility of policies and practices with evolving attitudes. It underscores the importance of addressing not only the formal rights of sexual minority groups but also the more subtle, yet significant forms of discrimination they may face.
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Introduction
In recent decades, favorable attitudes toward homosexuality have been on the rise in many parts of the world (Roberts, 2019). Despite this progress, sexual minority groups continue to experience persistent social stigma, as well as discriminatory laws, policies, and practices (Badgett & Crehan, 2016). These challenges contribute to elevated physical and mental health issues within these populations (National Academies of Sciences, Engineering, and Medicine, 2020; Russell & Fish, 2016).
Public attitudes toward homosexuality are complex and multifaceted (Adamczyk & Liao, 2019; Adolfsen et al., 2010), with existing research addressing a broad range of related topics. These include public displays of affection (Doan et al., 2014), civil rights and liberties (Lewis, 2003; Loftus, 2001), same-sex marriage (Baunach, 2011, 2012), adoption (Rye & Meaney, 2010), and biological basis of homosexuality (Lewis, 2009; Whitehead & Baker, 2012). However, it is crucial to recognize that public attitudes can vary substantially across these different dimensions. Between 1973 and 1998, Americans became increasingly supportive of gay and lesbian civil liberties, however, it was not until the 1990s that their views regarding the morality of homosexuality became more liberal (Loftus, 2001). Another study found inconsistent attitudes toward formal rights (e.g., partnership benefits) and informal privileges (e.g., public displays of affection) of same-sex couples, with variations depending on the respondents’ sexual orientation. Specifically, heterosexual respondents showed no preference for unmarried heterosexual couples over same-sex couples regarding formal rights but expressed less approval for informal privileges for same-sex couples; in contrast, lesbian and gay respondents exhibited a significant in-group preference for formal rights, but not for informal privileges (Doan et al., 2014). Additionally, previous studies have indicated differing attitudes toward gay men and lesbian women, with more unfavorable attitudes toward gay men (Einbinder et al., 2012; Herek, 2002; Stoever & Morera, 2007).
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These findings have prompted growing interests in exploring population heterogeneity in attitudes toward homosexuality or sexual minority, though research in this area remains relatively limited. A few studies have examined population heterogeneity based on four dimensions of sexual orientation beliefs: 1) naturalness (e.g., “Sexual orientation is innate”), 2) discreteness (e.g., “Sexual orientation is a category with clear boundaries: a person is either gay/lesbian, bisexual, or heterosexual”), 3) entitativity (e.g., “Individuals with the same sexual orientation seem to be connected to one another by some invisible link”), and 4) personal and social importance of identity (e.g., “It is possible to know about many aspects of a person once you know her or his sexual orientation”) (Grzanka et al., 2016; Tierney et al., 2021). Latent profile analyses consistently identified three belief profiles: 1) Naturalness-only, 2) Multidimensional essentialism, and 3) High discreteness, entitativity, and importance (Grzanka et al., 2016; Tierney et al., 2021). Similarly, another study classified university students’ attitudes toward gays and lesbians into three attitudinal groups: unbiased, moderately biased, and highly biased (Rutledge et al., 2012). While these studies attempted to differentiate between various dimensions of attitudes and explore population heterogeneity, no research to date has investigated the potential temporal shift in heterogeneity of attitudes.
Various factors have played a role in shaping public attitudes toward homosexuality. Previous studies consistently reported a sex difference, with males typically holding more negative attitudes toward homosexuality than females (e.g., Donaldson et al., 2017). This pattern may be attributed to males’ tendency to hold more traditional gender beliefs (Kite & Whitley 1996; Verweij et al., 2008). Investigations into social changes have found that younger generations were generally more egalitarian (Donaldson et al., 2017; Lee & Mutz, 2019), which is believed to be a driving force behind shifts in public attitudes. Studies of adolescents and young adults found mixed results regarding the relationship between age and attitudes (Feng et al., 2012; Horn, 2006; Jenkins et al., 2009), which may be due to the differences in examined dimensions. Other factors that support favorable attitudes toward homosexuality include non-heterosexual orientation (Gulevich et al., 2023; Verweij et al., 2008), higher education levels (Ohlander et al., 2005; Takács et al., 2016; Van den Akker et al., 2013), and lower levels of religiosity (Dotti Sani & Quaranta, 2020; Jäckle & Wenzelburger, 2015; Van den Akker et al., 2013). In addition to socio-demographic variables, studies indicated that increased contacts with sexual minority groups (Lewis, 2011; Skipworth et al., 2010), and greater sexual knowledge (Feng et al., 2012) can help mitigate negative stereotypes of homosexuality.
The cultural context of Chinese society, deeply influenced by Confucian values, is markedly distinct from that of Western societies. It is characterized by a paternalistic culture that emphasizes deference to hierarchical authority, places significant importance on family bonds, and prioritizes the needs of the community over individual interests (Adamczyk & Cheng, 2015). These values have further reinforced consensus and order in the society (Adamczyk & Cheng, 2015). A study based on four waves of Chinese General Social Survey (CGSS) found that while the percentage of people disapproving of same-sex sexual behaviors decreased by 5% during 2010–2017, a vast majority (79.9%) still held such views in 2017 (Lin & Wang, 2021). Several studies have highlighted the profound influence of cultural factors specific to Chinese society, such as filial piety, on individuals’ attitudes toward homosexuality (Feng et al., 2012; Lin, 2023; Lin et al., 2016). These findings underscore the importance of adopting culturally sensitive approaches when developing strategies to promote inclusion of sexual minority groups within the community.
Hong Kong, a special administrative region of China since 1997, has a unique socio-cultural environment that reflects its Chinese heritage, while also being shaped by its history as a former British colony. In Hong Kong, faith-based organizations play a significant role in the operation of social services, with approximately half of primary and secondary schools having religious affiliations, predominantly Christian (Jackson, 2015). In other words, Hong Kong faces sexual prejudices toward homosexuality stemming from both Confucian values, similar to the Mainland (Kwok & Wu, 2015), and Western Christian values (Wang et al., 2009; Zhou, 2006). At present, Hong Kong’s anti-discrimination ordinances do not extend to protections for sexual orientation or gender identity. In educational settings, policies and initiatives to combat homophobic and transphobic bullying are either absent or insufficiently implemented (Kwok, 2023). Sexual minority groups in Hong Kong face discrimination across various domains of life, including employment, housing, interactions with teachers and peers, and even within their own families (Pang et al., 2022; Suen & Wong, 2017). Beyond overt discrimination, diverse forms of microaggressions also persist (Kwok & Kwok, 2022). For instance, heteronormative assumptions and omissions of content related to LGBTQ + issues were pervasive in sexuality education curricula, workshops, and programs in Hong Kong (Chan, 2022). Such microaggressions have been associated with an increased risk of mental health problems, substance use, and suicidal behaviors among sexual minority populations (DeSon & Andover, 2024).
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Public attitudes toward homosexuality in Hong Kong have undergone progressive changes during the past decades. A 2006 survey of 2,024 Hong Kong residents revealed that over 40% of the respondents did not consider homosexuality to be “psychologically normal”, and half (51.4%) were unaccepting of having lesbian/gay family members (Home Affairs Bureau, The Government of the Hong Kong Special Administrative Region, 2006). However, data from a 2013 telephone survey showed a contrasting picture, with only 16% of the 410 respondents claimed that an individual’s sexual orientation would affect their acceptance of them, and 83% believed that parents should love their children regardless of their sexual orientation (Loper et al., 2014). A recent report in 2023 based on three waves of telephone surveys found that 60% of respondents supported same-sex marriage, which was a notable increase from 50.4% in 2017 and 38% in 2013 (Lau et al., 2023). Furthermore, 71% of respondents in 2023 believed Hong Kong should introduce laws to protect against sexual orientation-based discrimination, up from 69% in 2017 and 58% in 2013 (Lau et al., 2023).
In summary, the unique cultural characteristics of Chinese societies have shaped public attitudes toward homosexuality in ways that differ from those observed in Western societies. While trend analyses of these attitudes have been conducted in the Chinese settings, research specifically focusing on adolescents remains limited. This focus is crucial, as adolescents not only play a pivotal role in shaping peer relationships and the overall school climate through their attitudes but also serve as key drivers of social change and reliable indicators of a society’s future direction. Furthermore, existing studies in both Hong Kong and broader Chinese contexts have rarely considered the multidimensional nature of public attitudes toward homosexuality when examining temporal changes, nor have they explored the potential heterogeneity within the population. To fill these gaps, this study aims to achieve three objectives through a repeated cross-sectional survey conducted between 2011 and 2021: 1) to provide an updated understanding of current attitudes toward homosexuality among secondary school students in Hong Kong, while also tracking any temporal changes over a decade; 2) to discover potential heterogeneity among adolescents based on their responses to different dimensions of attitudes and examine how sex, age, parental responses to sexuality-related questions, and online sexual knowledge exposure are related to the heterogeneity; 3) to investigate whether and how these population heterogeneity had shifted between 2011 and 2021.
Methods
Data
The data used in this study were extracted from the latest three waves of the Youth Sexuality Study (YSS), which were conducted in 2011, 2016, and 2021. The YSS, employing a repeated cross-sectional design, is a territory-wide survey that has been conducted every five years since 1981 by the Family Planning Association of Hong Kong (FPAHK). It targets full-time students enrolled in Chinese-speaking secondary schools with the aim of monitoring the trends in their sexual attitudes, knowledge, and behaviors. The sample sizes of the three waves of data were 8,343, 3,907, and 3,776, respectively. Written informed consent to participate in the study was obtained from either the participants or their legal guardians, with clear assurance that participation was entirely voluntary and anonymous. To minimize the risk of bias, teachers were instructed to refrain from engaging with students during the survey process.
For data collection, YSS adopted a cluster sampling method with schools serving as the sampling unit. In 2021 and 2016, the four districts of Hong Kong (Hong Kong Island, Kowloon, New Territories West, and New Territories East) were employed as the sampling clusters, while the 2011 survey used education level as the basis for cluster selection. This change in the sampling method was due to the reform of the education system in Hong Kong, which restructured the length of different stages of education. Since 2012, Hong Kong has moved from a 3 + 2 + 2 + 3 academic structure (three years of junior secondary school, two years of senior secondary school, two years of matriculation course, and three years of university education) to a 3 + 3 + 4 structure (three years of junior secondary school, three years of senior secondary school, and four years of university education). As a result, there were changes in the age and sex composition across the three waves of data, with adolescents in 2011 being older (mean age = 15.43, SD = 2.03) and comprising a higher proportion of girls (48.52%) compared to the other two waves (in 2016: 42.59% girls, mean age = 15.26, SD = 1.93; in 2021: 44.50% girls, mean age = 14.76, SD = 1.68).
To ensure comparability across different years, we selected respondents aged 12 to 18, which comprised 96.22% of the entire sample. This age range is representative of secondary school students. Next, we used the sex and age composition of the 2016 sample as the reference to create weights for the 2011 sample. These weights were calculated for each sex-age group in 2011 by dividing the proportion observed in the 2016 sample by the corresponding proportion in the 2011 sample. Furthermore, to account for potential biases arising from imbalanced sample sizes, a stratified subsample (N = 3,600) was generated for 2021, using the 2016 sample as the reference as well.
Measures
Attitudes toward homosexuality were measured by six items, which can be divided into three dimensions: 1) general acceptance of homosexuality (“Do you accept male homosexuality?” and “Do you accept female homosexuality?”), 2) attitudes toward public display of affection between people of the same sex (“Do you accept public display of affection between two men?” and “Do you accept public display of affection between two women?”), 3) attitudes toward equal rights of homosexuality (“Do you agree that people of the same sex can legally marry?” and “Do you agree that people of the same sex can raise children?”). The six items were answered on a three-point scale (Yes, No, and No opinion).
In addition to sex and age, four other covariates were included in the analysis to investigate their potential relationships with the attitude patterns. Sexual orientation was one such variable, but its measurement varied across survey years. Specifically, in 2021, seven categories were used to measure sexual orientation (i.e., heterosexuality, homosexuality, bisexuality, pansexuality, asexuality, others, and don’t know), while in both 2016 and 2011, only four categories were used (i.e., heterosexuality, homosexuality, bisexuality, and don’t know). Despite these differences, we recoded sexual orientation into a three-category variable (i.e., heterosexuality, non-heterosexuality, and don’t know) by merging the options that indicated non-heterosexuality.
Given that greater sexual knowledge has been associated with more accepting attitudes toward homosexuality (Feng et al., 2012), we included three variables related to adolescents’ sexual knowledge as covariates. The first two examined the paternal and maternal responses to sexuality related questions raised by the respondent (1 = explained well, 2 = avoided answering, 3 = scolded the respondent, 4 = varying responses based on the questions, 5 = the respondent thought the parent could not answer, 6 = others). These two variables were recoded into binary variables (0 = didn’t explain well, 1 = explained well) by merging the option 2–6 due to the limited sample sizes for certain options. The third covariate was the frequency at which the respondent was exposed to sexual knowledge content online (1 = No, 2 = Seldom, 3 = Sometimes, 4 = Often). This covariate was only assessed in the 2021 survey.
Data Analysis
In line with the methodology employed in previous studies (Barth & Trübner, 2018; Sun et al., 2023), the present study utilized latent class modeling to capture complex patterns and changes in attitudes toward homosexuality among adolescents in Hong Kong. While traditional variable-centered analyses assume population homogeneity and examine changes in variables independently, latent class modeling offers three significant advantages: 1) it uncovers population heterogeneity by simultaneously analyzing patterns across multiple indicators from different domains; 2) by examining shifts in the prevalence of latent classes, latent class modeling provides a more comprehensive understanding of changes in population composition over time; 3) latent class modeling accounts for measurement error in latent classes, allowing for explicit modeling of potential misclassification.
First, three latent class analyses (LCAs) were performed to identify the patterns of attitudes toward homosexuality in 2011, 2016, and 2021, separately. LCA is a clustering technique used to discover unobserved subgroups (i.e., latent classes) within a population based on observed categorical variables (Lanza & Rhoades, 2013). Individuals in the same class share common characteristics that distinguish them from members of other classes. In each of the three waves, we gradually increased the number of classes to identify the optimal number of classes. The models were compared using various model fit indices: 1) Akaike Information Criterion (AIC), Bayesian Information Criterion (BIC), and adjusted BIC (aBIC), 2) Entropy, 3) Lo-Mendell-Rubin likelihood ratio test (LMR-LRT), 4) the percentage of the smallest class, and 5) the interpretation and parsimony of the model. Generally, models with smaller ICs and higher entropy are preferred. A significant LMR-LRT p-value (p < 0.05) indicates that the model with k classes outperforms the model with k-l classes. Moreover, the smallest class should comprise at least 5% of the total sample. Once the best class solution was identified, we visualized and interpreted the pattern of each class based on the item-response probabilities. The effects of covariates were tested using the three-step approach: first, the latent class model was constructed using only the indicator variables; next, the most likely class variable was generated based on the latent class posterior distribution derived from the first step; finally, the most likely class was regressed on the covariates using multinomial regression, while considering the potential misclassification in the second step (Asparouhov & Muthén, 2014). Only a small proportion of missing values, not exceeding 5%, was detected in the covariates. As a result, listwise deletion was employed to address these missing values.
Second, based on the results generated from separate LCAs, we applied multiple group latent class analysis (multiple group LCA) to the pooled sample, using survey year as the grouping variable. Multiple group latent class models vary in their forms based on the extent of similarity shared across groups, which is determined by 1) whether the same number of classes is identified across groups; 2) whether the item-response probabilities of the classes are assumed to be equal across groups (i.e., measurement invariance); 3) whether the sizes of latent classes are the same across groups (i.e., distributional homogeneity).
In comparative analyses, it is common practice to minimize heterogeneity (Siegers, 2018). When the number of classes and item-response probabilities are constrained to be equal across groups, the changes in class prevalence can be interpreted directly because the class memberships hold the same meaning across groups. When the item-response probabilities are allowed to vary across groups, interpreting changes in class prevalence would be challenging. Moreover, the constrained model is much more parsimonious with fewer estimated parameters, which reduces the likelihood of identification problems (Collins & Lanza, 2009). Therefore, it was recommended to restrict the item-response probabilities across groups whenever reasonable (Collins & Lanza, 2009). Measurement invariance is not necessarily an all-or-nothing choice, and it is possible that the number of classes is different across groups and measurement invariance holds for a subset of the classes or a subset of observed variables. The assumption of distributional homogeneity is unrealistic for our case, hence will not be considered in our analysis.
To determine whether measurement invariance held, we compared the constrained model with the model in which the item-response probabilities were freely estimated across groups. BIC, aBIC, and entropy were used to evaluate the model fits. However, it was suggested that the model selection should rely not only on the fit statistics but also on the patterns of the differences across groups (Collins & Lanza, 2009).
All the analyses were performed using Mplus 8.7.
Results
Descriptive Analysis
After excluding the cases with missing data on all the attitude indicators, the sample sizes were 3,600 (42.50% female, mean age = 15.07, SD = 1.75), 3,642 (42.48% female, mean age = 15.07, SD = 1.75), and 3,527 (48.60% female, mean age = 15.26, SD = 1.80) in 2021, 2016, and 2011, respectively. The descriptive statistics of the study variables are shown in Table 1.
Table 1
Descriptive statistics of studied variables
Variables
n (%) / M (SD)
Acceptance of male homosexuality
No
Yes
No opinion
2021
474 (13.18%)
2137 (59.43%)
985 (27.39%)
2016
943 (25.91%)
1623 (44.59%)
1074 (29.51%)
2011
1526 (43.29%)
1031 (29.25%)
968 (27.46%)
Acceptance of female homosexuality
No
Yes
No opinion
2021
393 (10.93%)
2211 (61.47%)
993 (27.61%)
2016
807 (22.19%)
1753 (48.21%)
1076 (29.59%)
2011
1235 (35.05%)
1259 (35.73%)
1030 (29.23%)
Acceptance of PDA between two men
No
Yes
No opinion
2021
641 (17.83%)
1835 (51.04%)
1119 (31.13%)
2016
1255 (34.51%)
1263 (34.73%)
1119 (30.77%)
2011
2020 (57.37%)
615 (17.47%)
886 (25.16%)
Acceptance of PDA between two women
No
Yes
No opinion
2021
492 (13.70%)
1997 (55.61%)
1102 (30.69%)
2016
1001 (27.54%)
1522 (41.87%)
1112 (30.59%)
2011
1566 (44.48%)
933 (26.50%)
1022 (29.03%)
Agreement with legalizing same-sex marriage
No
Yes
No opinion
2021
363 (10.11%)
2525 (70.31%)
703 (19.58%)
2016
647 (17.87%)
2207 (60.97%)
766 (21.16%)
2011
1045 (29.68%)
1628 (46.24%)
848 (24.08%)
Agreement with same-sex parenting
No
Yes
No opinion
2021
476 (13.26%)
2350 (65.46%)
764 (21.28%)
2016
717 (19.80%)
2137 (59.02%)
767 (21.18%)
2011
957 (27.20%)
1685 (47.90%)
876 (24.90%)
Sexual orientation
Heterosexuality
Non-heterosexuality
Don’t know
2021
2420 (68.02%)
604 (16.98%)
534 (15.01%)
2016
2864 (79.36%)
242 (6.71%)
503 (13.94%)
2011
2992 (85.49%)
167 (4.77%)
341 (9.74%)
Explained well to sexuality related questions (Father)
No
Yes
2021
2663 (74.36%)
918 (25.64%)
2016
2706 (75.48%)
879 (24.52%)
2011
2706 (78.14%)
757 (21.86%)
Explained well to sexuality related questions (Mother)
No
Yes
2021
2248 (62.58%)
1344 (37.42%)
2016
2266 (63.05%)
1328 (36.95%)
2011
2258 (64.96%)
1218 (35.04%)
Exposure to online sex knowledge content
No
Seldom
Sometimes
Often
2021
1277 (35.59%)
964 (26.87%)
1038 (28.93)
309 (8.61%)
Note. PDA public display of affection
Latent Class Analyses
Table 2 displays the model fit indices for three waves of LCA models. In each of the three years analyzed, high entropy values were observed, and the ICs decreased as the number of classes increased, providing limited information for model selection. The LMR-LRT supported a four-class model in 2021 and 2011, and a five-class model in 2016. However, after examining the patterns of the classes, we finally selected a four-class model for year 2021 and 2016, and a three-class model for year 2011 based on substantive interpretations of the latent classes. Further details on the model selection process are shown in the Appendix.
Table 2
Model fit indices derived from latent class analyses at each wave
AIC
BIC
aBIC
Entropy
LMR-LRT
Smallest group (%)
Year 2021
2-class model
29,608.63
29,763.35
29,683.91
0.96
0.00
41.26%
3-class model
25,908.82
26,143.99
26,023.25
0.97
0.00
17.06%
4-class model
24,577.74
24,893.36
24,731.31
0.97
0.00
11.34%
5-class model
23,752.30
24,148.37
23,945.01
0.97
0.68
10.93%
6-class model
23,325.27
23,801.80
23,557.13
0.98
0.08
4.90%
7-class model
22,906.42
23,463.40
23,177.42
0.98
1.00
4.77%
Year 2016
2-class model
36,882.58
37,037.59
36,958.15
0.94
0.00
47.80%
3-class model
32,210.80
32,446.42
32,325.67
0.96
0.00
25.39%
4-class model
31,102.96
31,419.17
31,257.12
0.96
0.00
16.71%
5-class model
30,214.25
30,611.07
30,407.71
0.96
0.00
8.52%
6-class model
29,627.73
30,105.15
29,860.48
0.95
1.00
9.53%
7-class model
29,184.46
29,742.49
29,456.51
0.95
0.84
7.02%
Year 2011
2-class model
38,817.83
38,972.04
38,892.60
0.89
0.00
40.97%
3-class model
34,614.95
34,849.34
34,728.60
0.93
0.00
27.29%
4-class model
33,851.08
34,165.65
34,003.60
0.95
0.00
11.80%
5-class model
33,161.55
33,556.31
33,352.95
0.92
0.82
12.03%
6-class model
32,696.49
33,171.44
32,926.77
0.93
0.88
10.27%
7-class model
32,250.49
32,805.63
32,519.66
0.93
0.48
7.30%
Note. AIC Akaike Information Criterion, BIC Bayesian Information Criterion, aBIC adjusted Bayesian Information Criterion, LMR-LRT Lo-Mendell-Rubin likelihood ratio test. The optimal solution is indicated in boldface
Figure 1 presents the conditional item probabilities of the six items across the latent classes. The first class, denoted as the intolerant class, exhibited overall unfavorable attitudes toward homosexuality, although there was relatively less negativity regarding equal rights. The second class, referred to as the neutral class, was characterized by an overall neutrality toward homosexuality and relatively positive attitudes toward equal rights. The third class, labeled as the inclusive class, was the most accepting among the classes. The fourth class was termed the partially inclusive class, whereby the respondents were less comfortable with public display of affection than those from the inclusive class. The four classes in 2021 and 2016 showed consistent patterns, and the intolerant and neutral classes in 2011 were shared with the other two years. Respondents in the inclusive class in 2011 were relatively conservative about public display of affection between people of the same sex.
Fig. 1
Item probabilities for the latent class models at each wave
×
Latent Class Analyses with Covariates
Similar trends were found in the covariate analyses of three waves’ data (Table 3). Females, older youth respondents, and respondents who self-identified as non-heterosexual were more likely to be in classes with more positive attitudes. Parental responses to sexuality related questions did not show any significant relationships with the attitude patterns.
Table 3
Covariate analyses at each wave
Covariates
Inclusive (ref) vs Intolerant
Inclusive (ref) vs Neutral
Inclusive (ref) vs Partial inclusive
Intolerant (ref) vs Neutral
Intolerant (ref) vs Partial inclusive
Neutral (ref) vs Partial inclusive
OR (95%CI)
Year 2021 (N = 3526)
Sex (ref: Male)
0.20 (0.15, 0.26)***
0.30 (0.24, 0.36)***
1.06 (0.83, 1.36)
1.51 (1.12, 2.03)**
5.40 (3.85, 7.58)***
3.59 (2.74, 4.70)***
Age
0.90 (0.85, 0.96)**
1.00 (0.95, 1.05)
0.92 (0.86, 0.99)*
1.11 (1.03, 1.19)**
1.02 (0.94, 1.12)
0.93 (0.86, 1.00)
Non-heterosexuality (ref: Heterosexuality)
0.54 (0.39, 0.76)***
0.53 (0.41, 0.69)***
0.59 (0.43, 0.82)**
0.98 (0.67, 1.44)
1.09 (0.70, 1.70)
1.12 (0.76, 1.64)
Don’t know (ref: Heterosexuality)
2.23 (1.62, 3.07)***
2.44 (1.90, 3.13)***
1.59 (1.14, 2.23)**
1.10 (0.81, 1.48)
0.71 (0.48, 1.05)
0.65 (0.47, 0.90)*
Explained well to sexuality related questions (Father)
1.08 (0.77, 1.50)
0.82 (0.63, 1.07)
0.75 (0.53, 1.08)
0.76 (0.53, 1.09)
0.70 (0.45, 1.10)
0.92 (0.62, 1.36)
Explained well to sexuality related questions (Mother)
1.05 (0.76, 1.44)
0.79 (0.62, 1.01)
0.79 (0.57, 1.09)
0.76 (0.54, 1.07)
0.76 (0.50, 1.15)
1.00 (0.70, 1.42)
Exposure to online sex knowledge content
0.81 (0.72, 0.91)***
0.56 (0.51, 0.61)***
0.71 (0.63, 0.81)***
0.69 (0.61, 0.79)***
0.88 (0.76, 1.03)
1.28 (1.12, 1.47)***
Year 2016 (N = 3538)
Sex (ref: Male)
0.37 (0.30, 0.46)***
0.59 (0.49, 0.72)***
1.11 (0.89, 1.40)
1.58 (1.28, 1.95)***
2.98 (2.32, 3.82)***
1.89 (1.50, 2.38)***
Age
0.84 (0.79, 0.89)***
0.90 (0.85, 0.95)***
1.01 (0.95, 1.08)
1.08 (1.02, 1.14)*
1.21 (1.13, 1.30)***
1.12 (1.05, 1.20)**
Non-heterosexuality (ref: Heterosexuality)
0.18 (0.11, 0.28)***
0.17 (0.11, 0.26)***
0.39 (0.27, 0.58)***
0.96 (0.53, 1.73)
2.24 (1.29, 3.90)**
2.34 (1.37, 4.01)**
Don’t know (ref: Heterosexuality)
1.10 (0.82, 1.46)
1.35 (1.03, 1.77)*
0.95 (0.67, 1.35)
1.23 (0.95, 1.60)
0.87 (0.62, 1.23)
0.71 (0.51, 0.98)*
Explained well to sexuality related questions (Father)
0.94 (0.71, 1.26)
1.15 (0.88, 1.49)
1.00 (0.74, 1.36)
1.21 (0.91, 1.62)
1.06 (0.75, 1.49)
0.87 (0.64, 1.20)
Explained well to sexuality related questions (Mother)
0.99 (0.75, 1.29)
0.80 (0.63, 1.02)
1.00 (0.76, 1.33)
0.81 (0.62, 1.06)
1.02 (0.74, 1.40)
1.26 (0.94, 1.68)
Year 2011 (N = 3423)
Sex (ref: Male)
0.39 (0.32, 0.48)***
0.67 (0.55, 0.82)***
1.71 (1.41, 2.07)***
Age
0.83 (0.79, 0.87)***
0.84 (0.79, 0.88)***
1.01 (0.96, 1.06)
Non-heterosexuality (ref: Heterosexuality)
0.09 (0.05, 0.18)***
0.12 (0.07, 0.23)***
1.29 (0.56, 2.96)
Don’t know (ref: Heterosexuality)
0.80 (0.58, 1.11)
1.35 (1.00, 1.84)
1.69 (1.26, 2.26)***
Explained well to sexuality related questions (Father)
1.31 (0.98, 1.74)
1.14 (0.85, 1.53)
0.87 (0.66, 1.16)
Explained well to sexuality related questions (Mother)
0.96 (0.74, 1.24)
0.82 (0.64, 1.06)
0.86 (0.66, 1.11)
Note. Significance at the 0.05, 0.01, and 0.001 levels is indicated by one, two, and three asterisks, respectively
In the comparisons between heterosexual adolescents and those uncertain about their sexual orientation, inconsistencies were observed across the three waves. In 2011, uncertain adolescents were more often classified into the neutral class rather than the intolerant class. In 2016, there was a higher likelihood of entering the neutral class instead of the inclusive or partially inclusive classes among this population. Furthermore, in 2021, uncertain adolescents displayed a relatively negative attitude toward homosexuality, being less likely to be in inclusive class than intolerant, neutral, and partially inclusive class, and less likely to be in partially inclusive class than neutral class.
Due to data restrictions, the examination of the effect of exposure to online sexual knowledge was limited to the 2021 sample. It was found that greater exposure was in general associated with being in a more positive class. Nonetheless, respondents with greater exposure were also more likely to be in the intolerant class than in the neutral class. There was no difference in the likelihood of being categorized into the intolerant class versus partially inclusive class.
Multiple Group Latent Class Analysis
Based on the results of the separate LCAs, a partial measurement invariance model was fitted to explore the changes of the classes across the three waves. In this model, the item probabilities for the four classes in 2016 were constrained to be equal to those in 2021. For 2011, only the parameters for the intolerant and neutral classes were set to be equal to the corresponding classes in the other two years, while the inclusive class was freely estimated. This invariance model (number of parameters = 82, BIC = 115,009.781, aBIC = 114,749.196, Entropy = 0.956) was further compared with the model with all the parameters freely estimated (number of parameters = 154, BIC = 115,105.461, aBIC = 114,616.069, Entropy = 0.959). Both the models have high entropy values, suggesting a high accuracy of classification. As depicted in Fig. 1, the classes to which we imposed constraints exhibited comparable patterns. Hence, despite the disagreement of BIC and aBIC, we opted for the constrained model.
The multiple group latent class model was illustrated in Fig. 2. From 2011 to 2021, there was a remarkable decrease from 41.37% to 12.23% in the proportion of intolerant class. In contrast, the percentage of neutral class remained relatively stable at around 27%−29%. Notwithstanding the different definition of inclusive class in 2011, it is evident that this class has expanded progressively over time, increasing from 29.50% in 2016 to 47.31% in 2021. Additionally, there was a slight reduction in the proportion of individuals belonging to the partially inclusive class, declining from 16.69% in 2016 to 13.12% in 2021.
Fig. 2
Item probabilities for the constrained multiple group latent class model
×
Discussion
Drawing on a territory-wide survey, our study provides the first results on attitudes toward homosexuality among secondary school students in Hong Kong. It is also a pioneering effort within the Chinese context to examine both the population heterogeneity in these attitudes and their temporal changes. Between 2011 and 2021, our findings revealed a growing acceptance of homosexuality among Hong Kong adolescents. This aligns with the Global Acceptance Index (GAI) trend for Hong Kong which indicates increasing acceptance of sexual minority populations (Flores, 2021). Despite the increase in global average level of acceptance, the GAI for Asia has shown minimal change over the past decades (Flores, 2021). Moreover, global divides and polarization persist, with 56 out of 175 countries and regions experiencing increases in acceptance of sexual and gender minority groups between 1981 and 2020, while 57 reporting a decline (Flores, 2021). These patterns highlight the importance of region- and culture-specific analyses, such as our study.
Throughout the three waves of data, the respondents exhibited varying degrees of approval with respect to different topics of homosexuality. On one hand, almost half of secondary school students had expressed their support for same-sex marriage and same-sex parenting by 2011, which may be ascribed to the increasing representations of sexual minority groups in the media and the progress of LGBT + rights globally. On the other hand, it was only as recent as 2021, the acceptance of public displays of affection between people of the same sex reached comparable levels. Given that the majority of the respondents were heterosexual, a possible explanation for this inconsistency is that as the gradual elimination of institutional discrimination, social interaction may become a more important site where dominant groups maintain their subtle advantages and informal privileges over minority groups (Doan et al., 2014; Harris, 2001; Schwalbe et al., 2000). Additionally, we found that male homosexuality was less accepted than female homosexuality among secondary school students, consistent with previous studies (Bettinsoli et al., 2020; J. Wang et al., 2022). The discourse of heteronormativity acknowledges only two genders that align with biological sex and considers sexual attraction between opposite genders as the only acceptable norm (Kitzinger, 2005); hence, homosexuality is socially constructed as a violation of gender roles (Herek, 2002). Although both sexes face social pressure from gender non-conforming behaviors, pressure for males is usually more intense (Roberts et al., 2013; Sirin et al., 2004; Spivey et al., 2018; Vandello et al., 2008). Furthermore, males often have fewer socially acceptable options for emotional and physical expression compared to females, leading society to perceive displays of affection or physical contact between males as less appropriate or acceptable (Lim, 2002).
As the results of the LCAs indicated, the patterns of attitudes toward homosexuality among secondary school students have undergone temporal changes over the years. In 2011, three classes (intolerant, neutral, and inclusive) were identified. In both 2016 and 2021, a four-class model was optimal, consisting of three classes similar to those observed in 2011 and a new “partially inclusive” class. Notably, members of the inclusive class in 2011 were less likely to express support than those in the later years, primarily manifested as a lower level of tolerance toward public displays of affection between people of the same sex. In 2011, non-accepting attitudes toward public displays of affection were mainstream among respondents; hence, an inclusive class that consistently showed support across aspects of attitudes may have been too small in size to emerge as a representative class. Over time, with the attitudes toward homosexuality becoming more positive, a partially inclusive class emerged in 2016 and 2021 samples. The inconsistency reflected in this class highlighted the less positive attitudes toward public visibility of homosexuality. To better interpret the changes across the three waves, we built a multiple group LCA with partial measurement invariance. The findings from this analysis further demonstrated that the secondary school students were becoming more inclusive: a “consistent” inclusive class emerged in 2016, and almost half of the respondents in 2021 belong to this class, while the intolerant class shrank by 25% over the decade. Interestingly, the proportion of neutral class remained stable across the three waves, suggesting the presence of a subgroup of secondary school students who had either not yet developed an awareness of social issues or were simply uninterested in them.
The covariate analyses showed that females, older respondents, and non-heterosexual respondents had a higher probability in classes with more favorable attitudes. According to the theory of hegemonic masculinity, males employ various means to establish and legitimize their dominant positions by promoting hegemonic masculinity (Connell, 1993; Connell & Messerschmidt, 2005). Consequently, males are more prone to resist behaviors that deviate from traditional gender roles and sexual patterns to maintain their societal advantages (Chi & Hawk, 2016). Age also emerged as a significant predictor of the attitude patterns in our study. During adolescence, individuals embark on a journey toward greater autonomy and independence and their parents’ influence starts to wane. They are exposed to a wider range of information sources and their cognitive abilities continue to develop, leading to a better understanding of their surroundings and a constantly evolving worldview. As a result, older adolescents tend to exhibit a greater degree of acceptance toward homosexuality, relative to their younger peers. It is unsurprising that non-heterosexual respondents showed more favorable attitudes toward homosexuality. However, it is worth noting that a small proportion of this population was classified into latent classes with non-accepting attitudes. This phenomenon may be attributed to internalized sexual stigma, wherein sexual minority individuals adopt negative societal attitudes toward their community as a part of their own value system (Herek et al., 2009). Such self-directed stigma may increase risks of mental health problems among sexual minority groups (Berg et al., 2015; Xu et al., 2017). In comparisons between heterosexual adolescents and those uncertain about their sexual orientation, the latter exhibited less positive attitudes toward homosexuality in 2016 and 2021, with a tendency toward neutrality observed in 2011. These differences may be attributed to the fact that the attitude classes identified in 2011 differed from those generated in the subsequent survey waves. One possible explanation for the greater tendency of uncertain adolescents to express negative/neutral views is that they may be in a process of questioning and exploring their sexual identity. Research has shown that questioning youth often experience higher levels of internalized stigma than other sexual minority youth (Watson et al., 2019). Alternatively, some of the uncertain adolescents may simply be less attuned to experiences involving sexual/romantic attraction/intimate relationship in general.
There was no significant relationship between parental responses to sexuality-related questions and the attitude patterns among secondary school students. In Chinese contexts, where traditional Confucian beliefs prevail, sexual orientation remains a sensitive topic between parents and children. Discussions related to sexual orientation may raise concerns regarding an individual’s ability to fulfill family responsibilities, such as marriage and having children (Wang & Zheng, 2021). Furthermore, stigma toward sexual minorities may extend to their parents, thereby causing shame and disgrace to their family (Choi & Luo, 2016). As a result, adolescents may find it difficult to discuss issues related to sexual orientation with their parents.
There appears to be a conflicting trend in the relationship between exposure to online sexual knowledge and the attitude patterns. Since we did not measure the exact content that respondents were exposed to, we can only provide a potential explanation for this phenomenon. On one hand, increased exposure to online sexual knowledge means more opportunities to learn about different sexual orientations, which may lead to more positive attitudes toward homosexuality. On the other hand, most current sex education programs are still framed from a heteronormative perspective, which may unconsciously convey a message that homosexuality is a deviation from the norm. As a result, some respondents with greater exposure to online sexual knowledge might fall into the intolerant class, rather than the neutral class.
Overall, our study provides updated insights into public attitudes toward homosexuality in Hong Kong, offering valuable guidance for policymakers and practitioners to evaluate whether their policies and practices align with the evolving societal views. While we observed increasing acceptance among Hong Kong adolescents, a notable portion still holds intolerant attitudes, underscoring the need for continued progress. To promote broader societal acceptance, legal efforts, beginning with anti-discrimination legislation for sexual minority groups, are crucial, as they lay the foundation for further institutional support. Moreover, as our study highlighted, modern prejudice can manifest in various forms. It is, therefore, essential not only to emphasize the formal rights of sexual minority groups but also to be mindful of more subtle yet significant forms of discrimination (Doan et al., 2014), such as microaggressions.
Limitations and Future Directions
This study has several limitations. First, the measurement of attitudes toward homosexuality was not exhaustive. Although scales have been developed to capture the multifaceted nature of the attitudes (Adolfsen et al., 2010), they have not yet been validated for use in the Chinese context. Future studies may benefit from developing or validating a multidimensional scale specifically tailored to the Chinese context, incorporating a wider range of dimensions for comparison and pattern analyses. Second, our analysis was restricted to a limited set of covariates. Future studies should investigate the influence of factors such as family socioeconomic status, parental attitudes toward homosexuality, and contact with sexual minority groups on the attitude patterns. Moreover, the way Chinese society perceives and approaches homosexuality issues is shaped by the importance of family kinship and the social boundaries between family members and outsiders (Yeo & Chu, 2018). A notable disparity in acceptance levels toward homosexuality was observed across different types of relationships: acceptance rates were substantially higher for co-workers (83.57%) and friends (76.92%) compared to relatives (40.19%) (Yeo & Chu, 2018). As such, future research could explore the potential impact of Chinese traditional values, such as emphasis on conformity and family harmony, on societal attitudes toward homosexuality in the Chinese context. Third, although we aligned the sex and age composition across years to enhance comparability, the changes in sampling methods may have introduced biases beyond our control. Nevertheless, to the best of our knowledge, our dataset represents the largest repeated cross-sectional survey investigating the changes in attitudes toward homosexuality among adolescents in Hong Kong. Fourth, our study may not be representative of the adolescent population in Hong Kong as students from non-Chinese speaking schools and evening schools were not included. However, no more than 6% of the day school students enrolled in non-Chinese speaking schools during 2010 and 2020 (Education Bureau, The Government of the Hong Kong Special Administrative Region, 2024), and the number was even lower for those attending evening schools. Fifth, given that our sample was limited to secondary school students in Hong Kong, our findings may not generalize to other population groups or socio-cultural contexts. Future research should extend to other age groups such as young adults or working adults across diverse occupations for a more comprehensive understanding of attitudes toward homosexuality in the general public. Investigating diverse socio-cultural contexts and age cohorts can help inform targeted strategies to reduce discrimination. Sixth, our study adopted a repeated cross-sectional design which limits our ability to examine within-person changes in attitudes over time. Future research could employ a longitudinal design and latent transition analysis to track individual-level changes. Finally, although the present study emphasized respondent anonymity and confidentiality and minimized teacher involvement during the survey process, the sensitive nature of the topic could induce social desirability bias in the responses and our results.
Declarations
Ethical approval
Ethical approval was obtained from the Human Research Ethics Committee of the University of Hong Kong (HREC Number = EA200333). The authors assert that all procedures contributing to this work comply with the ethical standards of the relevant national and institutional committees on human experimentation and with the Declaration of Helsinki in 1975, as revised in 2008.
Conflicts of Interest
None.
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