Next Article in Journal
Tobacco Use and Treatment among Cancer Survivors
Previous Article in Journal
The Evaluation of Municipal Waste in Counties in Poland with the Use of the Theory of Phenomena Spatial Concentration
 
 
Search for Articles:
Title / Keyword
Author / Affiliation / Email
Journal
Article Type
 
 
Advanced Search
 
Section
Special Issue
Volume
Issue
Number
Page
 
Journals
IJERPH
Volume 17
Issue 23
10.3390/ijerph17239108
ijerph-logo
Submit to this Journal Review for this Journal Propose a Special Issue
► Article Menu

Article Menu

share Share announcement Help format_quote Cite question_answer Discuss in SciProfiles thumb_up
...
Endorse textsms
...
Comment
first_page
settings
Order Article Reprints
Font Type:
Arial Georgia Verdana
Font Size:
Aa Aa Aa
Line Spacing:
Column Width:
Background:
Article

Social Capital and Self-Rated Health: Empirical Evidence from China

by
Jiafeng Gu
1,* and
Ruiyu Zhu
2
1
Institute of Social Survey Study, Peking University, Beijing 100871, China
2
Antai College of Economics and Management, Shanghai Jiao Tong University, Shanghai 200030, China
*
Author to whom correspondence should be addressed.
Int. J. Environ. Res. Public Health 2020, 17(23), 9108; https://doi.org/10.3390/ijerph17239108
Submission received: 2 November 2020 / Revised: 25 November 2020 / Accepted: 4 December 2020 / Published: 6 December 2020
(This article belongs to the Section Health Economics)
Versions Notes

Abstract

:
This study assesses the relationship between social capital and self-reported health (SRH) by comparing different genders and ages. It utilizes data from the 2016 China Family Panel Study data with a sample of 30,657 adult individuals from 25 provincial-level administrative regions in China. This was a cross-sectional study conducted with computer-assisted face-to-face interviews to assess social capital and self-rated health among Chinese adults. A multi-level Poisson regression model is employed to model social capital-related dependent variables using the independent variable of fair/poor health status. In terms of social relations, mobile phone use can improve men’s health. However, this effect is insignificant for women. Moreover, gender and age interact with the relationship between social capital and individual health. The relationship between trust and self-rated health is not significantly different between men and women. The frequency of feeling lonely and the lack of feelings for the community in which they live have a negative impact on self-rated health, but there are no obvious differences in terms of gender. The number of meals per week with family members is negatively correlated with men’s SRH, but there is no correlation with adult women 41 and above. Lack of help from neighbors is negatively correlated with men’s health, but not with that of adult women 40 and below. Being a member of the Chinese Communist Party or a member of the Chinese Communist Youth League is positively correlated with SRH for women 60 and above.

1. Introduction

The relationship between social capital and health has been a frequent topic of discussion in Western countries over the past two decades [1]. Social capital refers to the resources to which individuals and groups have access through their social networks [2,3]. Self-rated health (SRH) has been regarded as a valid health-status indicator [4,5,6]. The mechanisms and means of social capital’s impact on SRH are influenced by other factors, such as individual lifestyle [7], social norms [8] and politics and the economy [9]. Research had shown that gender plays an important role in the relationship between social capital and health [10,11], yet the mechanisms behind this are not well understood [12,13].
When studying the relationship between social capital and women’s’ health, most scholars report that social capital improves women’s health. Such findings have come out of Sweden [14], the United States [13], European countries [10] and Iran [15]. However, Ferlander et al. [16] found that social capital can be a mixed blessing for women. Silva et al. [17] found that there are inverse associations between mental health and individual level cognitive social capital. Thuy and Berry [18] also found that those mothers had only modest social capital, but the little they had tended to be correlated with better mental health. Amoah et al. [19] found that social capital obstructs efficient healthcare delivery and hurts female inpatients’ health in Ghana. Social capital has also been shown to damage women’s mental health in China [20]. Women tend to bear the cost of creating and maintaining social capital, while deriving fewer benefits from it than men [21]. Women also tend to maintain social capital by making phone calls, while men tend to maintain social capital by meeting in person [3]. However, little research has explored the divergent ways through which men and women maintain social capital.
Moreover, with the popularity of mobile phones, people often use these devices to keep in touch and maintain social capital [22]. There is a positive association between mobile phone usage and social capital [23,24,25]. Although existing literature has demonstrated that using a mobile can contribute to maintaining social capital, the variable effects of social capital maintained by mobile phone usage on women’s and men’s health have received little attention in the literature. There are gender differences in using mobile phones to maintain social capital, and women appear to use mobile phones to maintain social capital more than men [3]. However, despite the proliferation of mobile phones to keep in touch in modern society, evidence of their variable effects on women’s and men’s health via social capital maintenance is still lacking.
What is the mechanism behind social capital’s effect on health? Previous research does not provide a clear explanation. In addition, most research on the relationship between social capital and health has been conducted in a Western context. In-depth analysis of the mechanism of social capital on health in China has been scant. Research on social capital’s effect on Chinese women’s health has been even rarer. Therefore, conducting this research in China not only has important theoretical value, but also practical significance for improving women’s social capital and improving their health.
Based on national representative data, we explore the gender roles, gendered communication and age effects in the relationship between social capital and self-reported health in China, and how social capital might be promoted to enhance women’s health at different ages. We compare the results from China with those of European countries. This provides new evidence on Western-Oriental social capital. Our study not only elucidates how gender affects health in China, but also contributes to the international comparative literature on gender, health, and social capital.

2. Literature Review and Hypothesis Development

Social capital was originally a sociological concept. Its origin can be traced to the beginning of the twentieth century [26]. In the health field, the concept of social capital was discussed by Coleman [27], Putnam and Bowling [28] and Kawachi and Berkman [29]. In the existing studies, the operational definitions are inconsistent. This has led to problems in measuring social capital. For example, measurements in existing research do not reflect the multiple dimensions of social capital [30], and some studies only use two questions to measure social capital, oversimplifying the concept [31]. At present, a standardized definition and measurement of social capital has yet to emerge in the field of health research, and there has also been a lack of measurement tools that conform to all dimensions of social capital.
Most existing literature measures social capital by two metrics: social networks and social cohesion [3,10,20]. Thus, social relations, as it relates to social networks and social cohesion, are an important part of social capital [16]. Moreover, social capital is often divided into structural and cognitive domains [2]. Trust measures the structural domains of social capital and subjective feelings measure the cognitive domain [32,33]. Another dimension of social capital is organizational engagement. This can promote organizational social capital, a resource reflecting the character of social relations to the formal or informal organization [34].
How does social capital affect health? Lin Nan et al. have conducted a series of empirical studies on social capital’s effect on personal physical and mental health [35]. They believe that health is affected by stress and resources [36]. Social resources can buffer stress’s effect on health, thereby reducing the negative effects of negative life events on personal physical and mental health [37]. If the multiple dimensions of social capital are considered, then the effect of social capital on health will also have different paths. Although the definitions and measurements of social capital vary across studies, social relations, trust, subjective feelings and organizational engagement are important components of social capital [13,14,30,38]. Therefore, we can explore the path of social capital’s effects on health from these four perspectives.
Social capital is derived from resources embedded in social networks and is rooted in social relations [35,36]. In contemporary society, mobile phone is a convenient communication tool for maintaining social relationships [23]. Information about health promotion can proliferate through social communication circles via mobile phones, which promotes healthy habits [39]. In order to maintain their social circles, people need to socialize with others and have dinner together. As a result, dinners with family members will be less frequent. In other words, if you always eat at home and do not go out to socialize with others, your social network may shrink. In turn, you will obtain less positive information about health promotion from social relationships, which is adverse to your health. Neighborhood relations are an important part of social relations. Mutual help between neighbors can promote each other’s health [40]. Based on the above analysis of the path through which social capital influences health via social relations, our three hypotheses are:
Hypothesis 1.
Mobile phone use has a positive effect on SRH.
Hypothesis 2.
The frequency of family meals has a negative effect on SRH.
Hypothesis 3.
Lack of help from neighbors has a negative effect on SRH.
Social capital is a collection of resources in a social network, either actual or potential. It cannot exist without social trust [41]. When people believe that most others are selfish, it is easy to be suspicious. This is exhausting, physically and mentally, which is harmful to health [42]. On the contrary, trusting others can increase positive interpersonal interaction, which improves health [31,32,38]. In other words, social capital can provide emotional support to promote individuals’ health through social and psychological processes such as interpersonal trust and mutual respect. Based on the above analysis of the path through which social capital influences health via trust, we propose the following hypothesis:
Hypothesis 4.
Trusting others has a positive effect on SRH.
Social capital can be divided into two types: structural and cognitive. The former refers to an individual’s social network and various forms of social participation, while the latter refers to an individual’s subjective feelings about trust and reciprocity [7,18,29]. At the individual level, social capital often affects personal health through personal subjective feelings [31]. Those who lack social capital are prone to loneliness. This mental loneliness can impair their health [16]. In addition, social capital also affects individual health through community interaction. Community assistance helps improve health [43]. Based on the above analysis of the path through which social capital influences health via subjective feelings, we propose two hypotheses:
Hypothesis 5.
Feelings of loneliness have a negative effect on SRH.
Hypothesis 6.
Community attachment has a positive effect on SRH.
Organizational engagement, defined as a socially contextualized pattern of group belonging, is a form of organizational social capital [44]. Individuals with religious beliefs often participate in religious activities regularly. Communication between religious members can promote positive attitudes and contribute to health [45]. In addition, participating in the activities of political parties can also produce additional social capital, generating opportunities to use social resources to improve health [10]. Based on the above analysis of the path through which social capital influences health via organizational engagement, we propose two hypotheses:
Hypothesis 7.
Religious faith has a positive effect on SRH.
Hypothesis 8.
Communist party or youth league membership has a positive effect on SRH.
Social capital’s effect on health has been shown to be a source of gender disparities [11,12,46]. Therefore, this study will also test whether those above hypotheses are equally valid for male and female samples. The focus of this research is social capital’s effect on women’s health. Therefore, the discussion will focus more on whether the aforementioned hypotheses hold for the female sample. Age also mediates the relationship between social capital and health [47,48]. Individuals of different age groups have different types and levels of social capital, and their health also deteriorates with age. Therefore, this study will also examine social capital’s effect on women’s health in different age groups.

3. Methods

3.1. Data Description

The data used in this study come from the adult database of the 2016 China Family Panel Study (CFPS). Initiated in 2010, The China Family Panel Study is a nationwide, comprehensive longitudinal tracking survey conducted by the China Social Science Research Center (ISSS) at Peking University. It aims to reflect Chinese society and the Chinese economy by tracking data at the individual, family, and community levels to capture changes in population, education and health. The CFPS sample covers the population of 25 provinces/municipalities/autonomous regions in China mainland, with the exception of Xinjiang, Tibet, Qinghai, Inner Mongolia, Ningxia and Hainan. The population of these 25 provinces/municipalities/autonomous regions accounts for 95% of Mainland China’s population. CFPS mainly conducts face-to-face interviews aided by computer-assisted personal interviewing (CAPI). In situations where personal interviews are not feasible, telephone interviews using computer-assisted telephone interviewing (CATI) or Web interviews using computer-assisted Web interviewing (CAWI) are substituted.

3.2. Health Status

The self-evaluation of the respondents’ health status is this study’s dependent variable. In the survey, respondents were asked “How do you rate your own health status?” and were given five options: (1) excellent; (2) very good; (3) good; (4) fair and (5) poor. A fair and poor health binary variable was generated based on the health self-assessment: fair and poor values were 1, and the rest were 0.

3.3. Social Capital

In the public health field, social networks are defined as the extent of connectedness among groups in a society. It is a measure of the network of respondents, and there are three main variables. Credibility of information is important for connectedness among groups [42] and mobile communications, facilitated by mobility and portability of mobile computing can have a positive impact on individual social capital [49,50,51]. Nearly 90% of all respondents use mobile phones, so a monthly mobile phone bill is a good indicator to measure social interaction by mobile phone [51]. The degree of engagement with strong ties such as family members, and with weak ties such as neighbors, is relative to individual social capital [52]. As a result, the second variable is the number of dinners with family members during the week. Family meals are currently an important institution in Eastern and Western societies, serving as normative icons for collective eating [53]. Growing academic research has related family meals to a variety of health outcomes [54,55]. This is coded as an integer from 0 to 7. The third variable is neighbor help [56]. A binary variable of neighbor help was generated: no neighbor help was 0, and others were 1.
The second aspect of social capital is trust, the fundamental factor of social cohesion [20]. This study used one comprehensive variable to measure respondents’ degree of trust. In the survey, respondents were asked “Do you think most people can be trusted, or its better to be more careful with others?” The possible values were: (1) most people can be trusted, and (2) the more careful you are, the better. A trust binary variable was generated based on the answer of this question: the answer that most people can be trusted was 1, and the other was 0.The variable measures trust in the general sense [38]. Note that trust in the general sense measures not the willingness or ability of the respondent to trust, but the degree of trustworthiness of the surrounding environment, as perceived by the respondent.
Subjective feelings are another measure of social capital [33]. The first variable of subjective feeling is loneliness. Survey respondents were asked “Please indicate the frequency of feeling lonely in the past week according to your actual situation”. Possible values were: (1) almost never (less than one day); (2) sometimes (1–2 days); (3) often (3–4 days), and (4) most of the time (5–7 days). A binary variable of no feeling of loneliness was created where answer (1) was coded as 1 while others were coded as 0. The second variable was the level of feeling towards the community. Survey respondents were asked “Do you feel attachment towards the community you live in?” The possible values were: (1) strong attachment; (2) some attachment; (3) average attachment; (4) not much attachment, and (5) no attachment at all. A binary variable of attachment towards community was created where answer (5) was coded as 0 while others were coded as 1.
Finally, to measure organizational social capital, this study considers whether religious beliefs and Communist Party of China or Chinese Communist Youth League membership factor into social capital. YES was coded as 1 and NO was coded as 0.

3.4. Control Variables

The control variables added to the model in this study include age and its squared term, gender, marital status, employment status, and education level. Marital status options are: (1) married; (2) unmarried; (3) cohabitating; (4) divorced; and (5) widowed. Marriage was set as the baseline group. Employment status was categorized as: (1) employed; (2) unemployed; (3) in school; and (4) outside the labor market for other reasons. Employment was set as the baseline group. The educational attainment options were: (1) illiterate/semi-literate; (2) elementary school; (3) junior high school; (4) high school/secondary school/technical school/vocational high; (5) junior college; and (6) 4-year college or above. Illiterate/semi-literate was set as the baseline group. They are all binary variables. Moreover, provincial fixed effects are also included.

3.5. Model Selection

Most regression models used in the literature to estimate the prevalence ratio are either Poisson regression or log-binomial regression models [57]. In order to consider the possible differences between provinces, a multi-level Poisson regression model is used in this study [10]. This study uses a multi-level Poisson regression model, mainly for comparison with the results of Sara Pinillos-Franco and Ichiro Kawachi’s research [10]. They used a multi-level Poission regression model to analyze social capital’s effect on health in samples from 17 European countries. To facilitate the comparison between China and Europe, it is necessary to adopt the same research method with the same binary dependent variable.

3.6. Statistical Modelling

Listwise deletion to analyze complete cases would have resulted in a loss of 15.4% of the sample. Hence, we performed multiple imputations by creating an imputed dataset with the Markov chain Monte Carlo method in order to address potential bias due to missing data [58]. We assumed randomness in our missing variables. The lowest percentage of missing values was 0.09% for our dependent variable, and the highest was 5.32% on the item of neighbor help.
After multiple imputations of the missing values in the sample (n = 30,657), we reported descriptive statistics such as mean value and SD of relative variables in total sample, women’s sample (n = 15,352) and men’s sample (n = 15,305). Multi-level Poisson regression analysis was conducted to test each hypothesis in the theoretical model using R3.5.2, with p-value < 0.05 indicating statistical significance. The significance level was set at α = 0.05, and all tests were two-tailed.

4. Results

Table 1 reports the descriptive statistics of the variables. 33.5% of the respondents reported that their health was fair or poor. Among men, 29.3% reported that their health was fair or poor, while the proportion of women was 37.8%. This is consistent with many European countries [59]. The mean age of the sample was 46.092 years old, and the average age of women was slightly higher than that of men. The gender ratio in the sample is essentially equal. In terms of marital status, 76% of the sampled population was married. Men had higher rates of singleness and divorces than women, while women had higher rates of widowhood. A total of 70.5% of the samples were employed, and the male employment ratio was 78.1%, higher than that of women. The ratio of women exiting the labor market is 30.5%; for men, it was 15.8%.
In terms of social relations, the average monthly mobile phone bill is CNY 57.19, and men cost more than women. The average number of weekly dinners with family members was 5.581, and participants were more likely to think they could get help from their neighbors. In terms of trust, 56.3% of the samples believed that most people can be trusted. In terms of subjective feelings, 31.7% of the respondents reported feelings of loneliness; 67.9% of the sample felt attached towards the community.
Table 2 reports the prevalence and its 95% confidence interval estimates. The first column shows the results of the full sample, and the second and third columns are the regression results for individual males and females, respectively. To test the discrepancies between males and females, the interaction terms of social capital variables and the binary variable of males were included in model and the results are shown in column 4 of Table 2. As shown, males reported a 14.3% reduction in the fair and poor health status prevalence when compared to females. In terms of marital status, the unmarried demonstrated better health. In terms of employment, those who were employed were in better health. A higher level of education can also significantly improve health. Those with bachelor’s degrees or above had a reduced prevalence rate of 27.4%, compared to those who were illiterate or semi-literate. At the same time, the effect of education on health improvement was greater for females than males.
In terms of social relations, the average monthly mobile phone bill is associated with better health; It means that mobile phone usage can reduce the fair and poor health prevalence rate by 10.5%. However, this effect is not significant for women. Hypothesis 1 was confirmed only in the male sample, not in the female sample. The number of dinners with family members is inversely related to better health. The number of meals per week with family members is associated with a 1.8% increase in fair and poor health prevalence rate. Hypothesis 2 was thus confirmed. Neighbor help can promote health and hypothesis 3 was thus confirmed. As shown, the decline in trust in the general sense is negatively correlated with health, and this finding is consistent with our expectations [38]. Hypothesis 4 was thus confirmed. In terms of subjective feelings, the frequency of feeling lonely and the lack of attachment towards their community are negatively related to health status. Hypothesis 5 and 6 were thus confirmed. Religious beliefs can promote the health of men, while this relationship is not significant for women. Hypothesis 7 was confirmed only in the male sample, not in female sample. Being a member of the Chinese Communist Party or a member of the Chinese Communist Youth League is positively correlated with health status, and this effect is greater for males than females. Hypothesis 8 was thus confirmed. According to the regression coefficients of the interaction terms of the social capital variables and the male dummy variable, the effects of average monthly mobile phone bill, the attachment towards their community, and religious beliefs on health improvement were significantly greater for males than females.
Social capital’s effect on women’s health is age-specific [60,61]. To investigate the relationship between social capital and women’s health, we divided the sample of women into three groups according to age: women between 16 and 40, women between 41 and 60, and women over 60. Table 3 reports the estimated r prevalence rates for these three groups.
In terms of social relations, the average monthly mobile phone bill is insignificant for adult women of all ages. Moreover, the number of dinners with family members is only inversely correlated with better health among women 40 and younger. It is insignificant when women are 41 or above. In addition, lack of help from neighbors is negatively correlated with health among women aged 41 and older. It is insignificant when women are 40 or younger. Trusting others is positively correlated with better health only among women aged 60 or younger. The frequency of feeling lonely is negatively correlated with women’s health, while the attachment towards one’s community is positively correlated with women’s health. Being a member of the Chinese Communist Party or a member of the Chinese Communist Youth League is positively correlated health when women are 61 and above.

5. Discussion

Our research shows that some dimensions of social capital predict SRH differently for women versus men. This echoes the findings of previous research [10]. However, women’s SRH was not significantly affected by using mobile phones, while, for men, using mobile phones decreased their prevalence of fair/poor health by 10.5%. As previously discussed, relational use of mobile phones should have a positive effect on social capital, psychological well-being and health [24]. However, our research shows that this relationship only applies to men. Traditional wisdom believes that women like to use mobile phones to maintain social relations, while men like to maintain social capital through face-to-face communication [3]. Though the social capital maintained by usage of mobile phones can improve men’s health, it has no effect on women’s health at all.
Although mobile phones facilitate social capital maintenance, women derive less health benefits from them than men. It is possible that mobile phone usage might not increase women’s social capital. It is easier for women than men to be individualistic and alienated from society because of mobile phone overuse [60]. Additionally, women tend to incur higher health costs creating and maintaining social capital by mobile communication than do men. Studies have shown that feeling or perceiving cell phone ringers triggers more anxiety and depression in women than in men [24,49]. Mobile phones have been associated with stress and sleep disturbances among women, but not for men [49]. Females send more elaborate text messages than males [61]. Women also engage in long phone calls correlated with emotional and personal matters, while men tend to make short phone calls for specific purposes [49].
Women account for as much as 70% of the world’s impoverished population, and about two thirds of the world’s illiterate population [62]. Women also suffer worse health status outcomes than men along several parameters [10,18]. In response, policy makers have sought to implement interventions that empower women’s social capital, with the view that their health and welfare will benefit. Women are encouraged to use mobile phones to extend social networks associated with mutual support in their own communities in order to improve their health and overall quality of life. However, our research reveals that these interventions are only effective for men, because of gendered communication. The social capital maintained by using mobile phones has no effect on women. Thus, women should not be pushed to socialize with mobile phones under the guise of protecting their health.
The number of meals per week with family members is negatively correlated with men’s SRH. However, this form of social capital only negatively affects the SRH of adult women aged 40 or younger. Traditional wisdom on social capital suggests that women tend to be more family oriented, and this form of social capital has positive effects on women’s health [1,59]. However, this is inaccurate. Today, North American women are responsible for about two thirds of routine household tasks [63]. Chinese women face a similar situation. The heavy burden of housework is not only detrimental to women’s health, but also limits the development of women’s social capital outside the family, and even detracts from their work [64]. This negative effect may be diminished among women 41 or over because women’s work and social status have been relatively stable.
Lack of help from neighbors is negatively correlated with men’s health, but not for adult women 40 and below. Trusting others is positively correlated with better health among men, but only for women ages 60 and below. Feelings of loneliness and lack of attachment towards one’s community are both negatively correlated with men’s and women’s SRH. These findings show that gender and age mediate the relationship between social capital and SRH to a certain extent.
The relation between social capital and SRH may be universal, but many cultures will have variations. To European individuals, trust can improve both men and women’s SRH, while the effect of religious faith on men and women’s SRH is not significant [10]. Similar relations were confirmed by the present study, conducted in China. However, differences also exist. To European individuals, working in a political party improves only men’s SRH [10,59]. Meanwhile, in China, being a member of the Chinese Communist Party, or a member of the Chinese Communist Youth League is positively related to the SRH of men, and women aged 60 or older as well. Like men, Chinese women’s SRH can be improved by social capital from participation in politics. This is not the case in Europe. The emancipation and equality of women was one of the main platforms of the communist government of China when it came to power in 1949. This provided Chinese women with opportunities to accumulate social capital by participating in political activities, thus improving their health.
In the context of Confucian culture, individuals are more inclined to maintain and extend social capital through “strong relationships” (i.e., trust and obligation). In “strong relationships”, social interaction is a human relationship network rather than an information bridge, and the acquisition of health-related information is only a byproduct of human relationships [65]. Individuals in European and American societies tend to emphasize “weak ties” in social networks [66]. With weak ties, individuals acquire more heterogeneous knowledge and information. This benefits health based on a wide range of weak social interaction processes. In increasing social capital, mobile phones are an important way for Western societies to maintain weak social interaction. However, in China, in order to obtain valuable information, face-to-face interaction is often necessary. Confucian culture can influence Chinese women’s social style and make them more conservative in social interaction. Because of these reasons, it is difficult for social capital to influence the health of Chinese women via mobile phones. Moreover, the religious beliefs of the Chinese people are utilitarian and lack a sense of repentance, which contrasts with the religious sentiments of Westerners [67]. Therefore, it is difficult for social capital to influence the health of Chinese women via religious beliefs.
In summary, for women, social capital can have a positive effect on health through the following paths: (1) deriving health benefits through socializing with people outside the family; (2) creating a healthy community atmosphere through the mutual help of neighbors; (3) deriving emotional support from trust; (4) accepting and following healthy behavior norms by reducing loneliness and attaching more on the community; (5) strengthening positive values to maintain good mental health by joining the Communist Party or Youth League. For men, in addition to the aforementioned paths, social capital can also improve health by expediting the diffusion of health information on social networks through the use of mobile phones.
This study presents some limitations. First, data are only from China. Therefore, the relationship between social capital and SRH cannot be tested across Asian countries due to lack of data. Second, though several factors were controlled to identify the association between social capital and SRH, factors such as family members’ SRH, family history of illnesses, or social support were not controlled. Third, because this was a cross-sectional study, the establishment of cause-and-effect relationships between social capital and SRH remains limited. These are also issues that need further research in the future.

6. Conclusions

This is a study of the disparities between men’s and women’s SRH with respect to dimensions of social capital. It offers new insights into social capital’s effect on SRH among both men and women. This study used the CFPS (2016) adult database to explore gender differences in the relationship between social capital and health. A common argument in the women’s social capital literature is that using a mobile phone empowers women’s social capital and improves their health. This is because women tend to use mobile phones to maintain social capital more than men [3]. However, this is not the case. Our results show that mobile phone usage reduces the prevalence of fair and poor health status by 10.5% among males. However, this factor was insignificant for females. The number of meals per week with family members is negatively correlated with men’s SRH. However, this form of social capital only negatively affects the SRH of adult women aged 40 or younger. Lack of help from neighbors is negatively correlated with men’s health, but not for adult women 40 and below. Moreover, the results indicate that age mediates the relationship between social capital and individual health. Finally, political party participation improves health for men, but only for women over 60. This is different from Europe.
In summary, these findings on the relationship between social capital and health deviate from previous research in terms of the form of social capital, gender difference, gendered communication and demographic variables such as age that constitute the framework of the studies under different cultural backgrounds. These results have implications for global public health policy on improving women’s health.

Author Contributions

J.G. conceptualized the study. R.Z. finished the data analysis. J.G. prepared the first draft of the manuscript and played a major role in structuring arguments and smoothing out the text. All authors have read and agreed to the published version of the manuscript.

Funding

The authors disclose receipt of the following financial support for the research, authorship, and/or publication of this article: This research is funded by the National Social Science Foundation of China (17BSH122).

Acknowledgments

The authors gratefully acknowledge the Social Science Foundation of China (17BSH122) for support of this research. We would like to express our thanks to the editor and three anonymous reviewers for their insightful comments and suggestions. Access to data: J.G. and R.Z. had full access to all data in the study and take responsibility for the integrity of the data and the accuracy of the data analysis.

Conflicts of Interest

The authors declare no conflict of interest.

References

  1. Moore, S.; Kawachi, I. Twenty years of social capital and health research: A glossary. J. Epidemiol. Commu. H. 2017, 71, 513–517. [Google Scholar] [CrossRef] [PubMed]
  2. Cohen-Cline, H.; Beresford, S.A.; Barrington, W.; Matsueda, R.; Duncan, G.E. Associations between social capital and depression: A study of adult twins. Health. Place 2018, 50, 162–167. [Google Scholar] [CrossRef] [PubMed]
  3. Bourdieu, P. Musculine Domination; Stanford University Press: Stanford, CA, USA, 2001. [Google Scholar]
  4. Kim, J.; Lee, R.; Shim, J. Material hardship and self-rated health among low-income households in South Korea. Asia Pac. J. Soc. Work 2018, 28, 1–16. [Google Scholar] [CrossRef]
  5. Amoah, P.A. The Relationship between functional health literacy, self-rated health, and social support between younger and older adults in Ghana. Int. J. Environ. Res. Public Health 2019, 16, 3188. [Google Scholar] [CrossRef] [Green Version]
  6. Gu, J.; Ming, X. Perceived social discrimination, socioeconomic status, and alcohol consumption among Chinese adults: A nationally representative study. Int. J. Environ. Res. Public Health 2020, 17, 6043. [Google Scholar] [CrossRef]
  7. Xue, X.; Cheng, M. Social capital and health in China: Exploring the mediating role of lifestyle. BMC Public Health 2017, 17, 863–874. [Google Scholar] [CrossRef] [Green Version]
  8. Olamijuwon, E.O.; Odimegwu, C.O.; Wet, N.D. Social cohesion and self-rated health among adults in South Africa: The moderating role of race. Health. Place 2018, 51, 89–96. [Google Scholar] [CrossRef]
  9. Lindström, C.; Rosvall, M.; Lindström, M. Socioeconomic status, social capital and self-reported unmet health care needs: A population-based study. Scand. J. Public Health 2017, 45, 212–221. [Google Scholar] [CrossRef]
  10. Pinillos-Franco, S.; Kawachi, I. The relationship between social capital and self-rated health: A gendered analysis of 17 European countries. Soc. Sci. Med. 2018, 219, 30–35. [Google Scholar] [CrossRef]
  11. Jung, M.S.; Lee, K.S.; Kim, M.; Yun, H. Gender-specific relationship between executive function and self-rated health. Osong. Public. Health. Res. Perspect 2019, 10, 93–101. [Google Scholar] [CrossRef]
  12. Eriksson, M.; Ng, N.; Weinehall, L.; Emmelin, M. The importance of gender and conceptualization for understanding the association between collective social capital and health: A multilevel analysis from northern Sweden. Soc. Sci. Med. 2011, 73, 264–273. [Google Scholar] [CrossRef]
  13. Dean, L.; Subramanian, S.V.; Williams, D.R.; Armstrong, K.; Kawachi, I. The Role of social capital in African-American women’s use of mammography. Soc. Sci. Med. 2014, 104, 148–156. [Google Scholar] [CrossRef] [Green Version]
  14. Sundquist, K.; Yang, M. Linking social capital and self-rated health: A multilevel analysis of 11,175 men and women in Sweden. Health. Space 2007, 13, 324–334. [Google Scholar] [CrossRef]
  15. Baheiraei, A.; Bakouei, F.; Mohammadi, E. Social networks and health in Women: Results from a qualitative study in Iran. Cur. Women. Health. Rev. 2016, 12, 130–136. [Google Scholar] [CrossRef]
  16. Ferlander, S.; Stickley, A.; Kislitsyna, O.; Jukkala, T.; Carlson, P.; Mäkinen, I.H. Social capital—A mixed blessing for women? A cross-sectional study of different forms of social relations and self-rated depression in Moscow. BMC Psychol. 2016, 4, 37–49. [Google Scholar] [CrossRef] [Green Version]
  17. Silva, M.J.D.; Huttly, S.R.; Harpham, T.; Kenward, M.G. Social capital and mental health: A comparative analysis of four low income countries. Soc. Sci. Med. 2007, 64, 5–20. [Google Scholar] [CrossRef]
  18. Thuy, N.T.M.; Berry, H.L. Social capital and mental health among mothers in Vietnam who have children with disabilities. Glob. Health. Action 2013, 6, 18886. [Google Scholar] [CrossRef] [Green Version]
  19. Amoah, P.A.; Koduah, A.O.; Gyasi, R.M. “Who’ll do all these if I’m not around?” Bonding social capital, health and well-being of inpatients. Int. J. Qual. Stud. Heal. 2018, 13, 1435108. [Google Scholar] [CrossRef] [Green Version]
  20. Yiwen, Z.; Junfeng, J. Social capital and health in China: Evidence from the Chinese general social survey 2010. Soc. Indic. Res. 2019, 142, 411–430. [Google Scholar]
  21. Sapiro, V. Gender, social capotal and politics. In Gender and Social Capital; O’Neil, B., Gidengil, E., Eds.; Routledge: New York, NY, USA, 2006; pp. 151–183. [Google Scholar]
  22. Haider, I.; Gujjar, A.A.; Juni, S.M.; Kareem, J. Impact of cell phones on social capital of university students: A case of Bzu-Bahadur campus, Layyah, Asian. J. Basi. Appl. Sci 2014, 12, 44–49. [Google Scholar]
  23. Chan, M. Mobile phones and the good life: Examining the relationships among mobile use, social capital and subjective well-being. New. Media. Soc. 2015, 17, 96–113. [Google Scholar] [CrossRef]
  24. Chen, H.T.; Li, X. The contribution of mobile social media to social capital and psychological well-being: Examining the role of communicative use, friending and self-disclosure. Comput. Hum. Behav. 2017, 75, 958–965. [Google Scholar] [CrossRef]
  25. Hampton, K.N.; Lee, C.J.; Her, E.J. How new media affords network diversity: Direct and mediated access to social capital through participation in local social settings. New. Media. Soc. 2011, 13, 1031–1049. [Google Scholar] [CrossRef] [Green Version]
  26. Hanifan, L.J. Social capital–Its development and use. In The Community Centre; Hanifan, L.J., Ed.; Silver Burdett: Boston, MA, USA, 1920; pp. 78–90. [Google Scholar]
  27. Coleman, J.S. Foundations of Social Theory; The Belknap Press of Harvard University Press: Cambridge, MA, USA, 1990. [Google Scholar]
  28. Putnam, R.D.; Bowling, A. The Collapse and Revival of American Community; Simon and Schuster: New York, NY, USA, 2000. [Google Scholar]
  29. Kawachi, I.; Berkman, L.F. Social Capital, Social Cohesion, and Health; Oxford University Press: Oxford, UK, 2014. [Google Scholar]
  30. Lochner, K.A.; Kawachi, I.; Kennedy, B.P. Social capital: A guide to its measurement. Health Place 1999, 5, 259–270. [Google Scholar] [CrossRef] [Green Version]
  31. Kim, J.Y.; Yoon, J.; Kim, M.H.; Kim, S.S. Association between interpersonal trust, reciprocity, and suicidal behaviors: A longitudinal cohort study in South Korea. Prev. Med. 2017, 99, 218–221. [Google Scholar] [CrossRef]
  32. Wang, H.; Schlesinger, M.; Wang, H.; Hsiao, W.C. The flip-side of social capital: The distinctive influences of trust and mistrust on health in rural China. Soc. Sci. Med. 2009, 68, 133–142. [Google Scholar] [CrossRef]
  33. Dean, W.R.; Sharkey, J.R. Food insecurity, social capital and perceived personal disparity in a predominantly rural region of Texas: An individual-level analysis. Soc. Sci. Med. 2011, 72, 1454–1462. [Google Scholar] [CrossRef] [Green Version]
  34. Framke, E.; Sørensen, O.H.; Pedersen, J.; Clausen, T.; Rugulies, R. Effect of a participatory organizational workplace intervention on workplace social capital: Post-hoc results from a cluster randomized controlled trial. BMC Public. Health 2019, 19, 693–703. [Google Scholar] [CrossRef] [Green Version]
  35. Lin, N.; Dean, A.; Ensel, W.M. Social Support. and Depression; Academic Press: New York, NY, USA, 1986. [Google Scholar]
  36. Lin, N.; Ensel, W.M. Life stress and health: Stressors and resources. Am. Sociol. Rev. 1989, 54, 382–399. [Google Scholar] [CrossRef]
  37. Lin, N.; Ensel, W.M.; Simeone, R.S.; Kuo, W. Social support, stressful life events, and illness: A model and an empirical test. J. Health Soc. Behav. 1979, 20, 108–119. [Google Scholar] [CrossRef]
  38. Abbott, S.; Freeth, D. Social capital and health: Starting to make sense of the role of generalized trust and reciprocity. J. Health. Psychol. 2008, 13, 874–883. [Google Scholar] [CrossRef] [PubMed]
  39. Patrick, K.; Griswold, W.G.; Raab, F.; Intille, S.S. Health and the mobile phone. Am. J. Prev. Med. 2008, 35, 177–181. [Google Scholar] [CrossRef] [PubMed]
  40. Beaudoin, C.E. Bonding and bridging neighborliness: An individual-level study in the context of health. Soc. Sci. Med. 2009, 68, 2129–2136. [Google Scholar] [CrossRef] [PubMed]
  41. Burt, R.S.; Hogarth, R.M.; Michaud, C. The social capital of French and American managers. Organ. Sci. 2000, 11, 123–147. [Google Scholar] [CrossRef] [Green Version]
  42. Jang, K.; Baek, Y.M. When information from public health officials is untrustworthy: The use of online news, interpersonal networks, and social media during the MERS Outbreak in South Korea. Health. Commun. 2018, 34, 1–8. [Google Scholar] [CrossRef] [PubMed]
  43. Hyyppa, M.; Maki, J. Individual-level relationships between social capital and self-rated health in a bilingual community. Prev. Med. 2001, 32, 148–155. [Google Scholar] [CrossRef] [PubMed]
  44. Son, J. Institutional affiliation as a measure of organizational social capital: A case study of Korea. Soc. Indic. Res. 2016, 129, 699–716. [Google Scholar] [CrossRef]
  45. Strawbridge, W.J.; Shema, S.J.; Cohen, R.D.; Kaplan, G.A. Religious attendance increases survival by improving and maintaining good health behaviors, mental health, and social relationships. Ann. Behav. Med. 2001, 23, 68–74. [Google Scholar] [CrossRef]
  46. Burt, R.S. The gender of social capital. Ration. Soc. 1998, 10, 5–46. [Google Scholar] [CrossRef]
  47. Yuanyuan, L.; Changgui, K.; Wei, B.; Wanqing, H.; Weiying, Y.; Yan, S.; Xinyu, L.; Wenjun, L. Trends in diabetes mortality by gender in urban and rural areas in China from 2003 to 2012: An age-period-cohort analysis. Asia. Pac. J. Public. Health 2019, 31, 238–245. [Google Scholar]
  48. Field, D. Continuity and change in friendships in advanced old age: Findings from the Berkeley Older Generation Study. Int. J. Aging Hum. Dev. 1999, 48, 325–346. [Google Scholar] [CrossRef] [PubMed]
  49. Sekhon, A. Gender differences in mobile phone addiction and its association with stress among medical students. Indian. J. Health. Wellbeing 2018, 9, 232–234. [Google Scholar]
  50. Thomée, S.; Härenstam, A.; Hagberg, M. Mobile phone use and stress, sleep disturbances, and symptoms of depression among young adults—A prospective cohort study. BMC. Public. Health 2011, 11, 1–11. [Google Scholar] [CrossRef] [PubMed] [Green Version]
  51. Chen, B.; Liu, F.; Ding, S.; Ying, X.; Wang, L.; Wen, Y. Gender differences in factors associated with smartphone addiction: A cross-sectional study among medical college students. BMC Psychiatry 2017, 17, 341. [Google Scholar] [CrossRef] [PubMed] [Green Version]
  52. Kim, H.H.S. The association between social capital measures and self-reported health among Muslim majority nations. Int. J. Public. Health 2014, 59, 749–757. [Google Scholar] [CrossRef]
  53. Walton, K.; Ken, P.K.; Sheryl, L.R.-S.; Nicholas, J.H.; Matthew, W.G.; Field, A.E.; Austin, S.B.; Neumark-Sztainer, D.; Haines, J. Secular trends in family dinner frequency among adolescents. BMC. Rec. Notes 2016, 9, 35. [Google Scholar] [CrossRef] [PubMed] [Green Version]
  54. Fulkerson, J.A.; Story, M.; Mellin, A.; Leffert, N.; Neumark-Sztainer, D.; French, S.A. Family dinner meal frequency and adolescent development: Relationships with developmental assets and high-risk behaviors. J. Adolesc. Health 2006, 39, 337–345. [Google Scholar] [CrossRef]
  55. Martinasek, M.P.; DeBate, R.D.; Walvoord, A.G.; Melton, S.T.; Himmelgreen, D.; Allen, T.D.; McDermott, R.J. Using social marketing to increase the frequency of the family dinner. Ecol. Food. Nutr. 2010, 49, 431–451. [Google Scholar] [CrossRef]
  56. Hoogerbrugge, M.M.; Burger, M.J. Neighborhood-based social capital and life satisfaction: The case of Rotterdam, The Netherlands. Urban. Geogr. 2018, 39, 1484–1509. [Google Scholar] [CrossRef] [Green Version]
  57. Espelt, A.; Marí-Dell’Olmo, M.; Penelo, E.; Bosque-Prous, M. Applied prevalence ratio estimation with different regression models: An example from a cross-national study on substance use research. Adicciones 2016, 29, 105–112. [Google Scholar] [CrossRef] [Green Version]
  58. Schunk, D. A Markov chain Monte Carlo algorithm for multiple imputation in large surveys. Asta. Adv. Stat. Anal. 2008, 92, 101–114. [Google Scholar] [CrossRef] [Green Version]
  59. Bambra, C.; Pope, D.; Swami, V.; Stanistreet, D.; Roskam, A.; Kunst, A.; Scott-Samuel, A. Gender, health inequalities and welfare state regimes: A cross-national study of 13 European countries. J. Epidemiol. Commun. H. 2009, 63, 38–44. [Google Scholar] [CrossRef] [PubMed] [Green Version]
  60. Norris, P.; Ronald, I. Gendering social capital: Bowling in women’s leagues? In Gender and Social Capital; O’Neil, B., Gidengil, E., Eds.; Routledge: New York, NY, USA, 2006; pp. 73–98. [Google Scholar]
  61. Kasesniemi, E.; Rautiainen, P. Mobile culture of children and teenagers in Finland. In Perpetual Contact: Mobile Communication, Private Talk, Public Performance; Katz, J.E., Aakhus, M.A., Eds.; Cambridge University Press: Cambridge, UK, 2002; pp. 170–192. [Google Scholar]
  62. Swindle, J. Feminization of Poverty. In Encyclopedia of Global Justice; Chatterjee, D.K., Ed.; Springer: Dordrecht, The Netherlands, 2012; pp. 347–348. [Google Scholar]
  63. Lachance-Grzela, M.; Bouchard, G. Why do women do the lion’s share of housework? A decade of research. Sex. Roles 2010, 63, 767–780. [Google Scholar] [CrossRef]
  64. Begoña, Á.; Daniel, M.-T. Time allocation and women’s life satisfaction: Evidence from Spain. Soc. Indic. Res. 2016, 129, 1–24. [Google Scholar]
  65. Zhao, L.; Roper, J. A Confucian approach to well-being and social capital development. J. Manag. Dev. 2011, 30, 740–752. [Google Scholar] [CrossRef]
  66. Sharone, O. Social capital activation and job searching: Embedding the use of weak ties in the American institutional context. Work. Occup. 2014, 41, 409–439. [Google Scholar] [CrossRef]
  67. Sorensen, B.; Nielsen, B.B. Social capital as it pertains to international ventures in Asia: A comparative study of Theravada Buddhist Laos and Confucian China. Int. J. Cross. Cult. Manag. 2018, 18, 221–240. [Google Scholar] [CrossRef]
Table
Table 1. Descriptive statistics.
Table 1. Descriptive statistics.
VariablesTotalMenWomen
MeanSDMeanSDMeanSD
Fair or Poor Health #0.3350.4720.2930.4550.3780.485
Social Relations
Mobile Phone Bill57.18559.07567.76266.96546.60447.659
Weekly Dinners with Family Members5.5812.5275.3372.6515.8242.373
Neighbor Help #0.6090.4880.6140.4870.6040.489
Trust
Trust Others #0.5630.4960.5790.4940.5480.498
Subjective Feelings
No Feelings of Loneliness #0.6830.4650.6980.4590.6690.471
Attachment Towards Community #0.6790.4670.6850.4640.6720.470
Organizational Engagement
Has Religious Faith #0.1440.3510.1190.3240.1680.374
Communist Party or Youth League Member #0.2050.4040.2340.4230.1770.382
Household Income (per capita)218676277822511652092122660256
Age46.09217.64745.76417.36046.41917.922
Male (ref. Female) #0.4990.5001.0000.0000.0000.000
Marriage Status (ref. Married)
Unmarried #0.1510.3580.1810.3850.1210.327
Co-habitating #0.0040.0610.0040.0640.0030.057
Divorced #0.0180.1330.0230.1500.0130.113
Widow #0.0670.2490.0360.1850.0970.296
Employment Status (ref. Employed)
Unemployed #0.0110.1040.0110.1050.0110.103
Exited Labor Market #0.2320.4220.1580.3640.3050.460
Studying #0.0520.2230.0500.2180.0540.227
Level of Education (ref. Illiterate or Semi-illiterate)
Elementary School #0.2110.4080.2300.4210.1920.394
Junior High #0.2830.4500.3160.4650.2500.433
High School/Secondary School/Technical School/Vocational School #0.1430.3510.1600.3670.1270.333
Junior College #0.0590.2360.0620.2400.0570.232
Bachelor’s Degree or Higher #0.0410.1990.0460.2090.0370.189
Notes: the number of total sample, men sample and women sample is 30,657, 15,305 and 15,352; # indicates binary variables.
Table
Table 2. Prevalence of reporting fair and poor health values for the whole sample, and for women and men separately.
Table 2. Prevalence of reporting fair and poor health values for the whole sample, and for women and men separately.
VariablesPR (95%CI)PR (95%CI)PR (95%CI)PR (95%CI)
TotalMenWomenTotal
Constant0.025 *** (0.018–0.034)0.020 *** (0.013–0.031)0.025 *** (0.017–0.039)0.024 *** (0.017–0.032)
Social Relations
Mobile Phone Bill0.892 *** (0.871–0942)0.895 *** (0.874–0.951)1.003 (0.999–1.005)1.000 (0.999–1.000)
Mobile Phone Bill*Male 0.999 *** (0.998–1.000)
Weekly Dinners with Family Members1.018 *** (1.011–1.026)1.026 *** (1.015–1.038)1.012 ** (1.002–1.022)1.015 *** (1.005–1.025)
Weekly Dinners with Family Members*Male 1.007 (0.993–1.021)
Neighbor Help0.936 *** (0.906–0.967)0.918 *** (0.872–0.966)0.952 ** (0.914–0.992)0.956 ** (0.918–0.996)
Neighbor Help*Male 0.952 (0.893–1.016)
Trust
Trust Others0.882 *** (0.855–0.909)0.895 *** (0.853–0.939)0.875 *** (0.841–0.909)0.872 *** (0.839–0.907)
Trust Others*Male 1.025 (0.964–1.089)
Subjective Feelings
No Feelings of Loneliness0.724 *** (0.702–0.747)0.732 *** (0.696–0.770)0.725 *** (0.697–0.754)0.723 *** (0.695–0.752)
No Feelings of Loneliness*Male 1.005 (0.945–1.069)
Attachment Towards Community0.836 *** (0.810–0.864)0.808 *** (0.767–0.850)0.861 *** (0.825–0.897)0.864 *** (0.829–0.901)
Attachment Towards Community*Male 0.928 ** (0.869–0.991)
Organizational Engagement
Has Religious Faith0.992 (0.952–1.035)0.936 *(0.866–1.010)1.028 (0.978–1.081)1.025 (0.975–1.076)
Has Religious Faith*Male 0.913 ** (0.836–0.998)
Communist Party or Youth League Member0.898 *** (0.854–0.944)0.866 *** (0.810–0.926)0.936 * (0.867–1.011)0.903 *** (0.838–0.974)
Communist Party or Youth League Member*Male 0.989 (0.898–1.088)
Household Income(per capita)1.000 (1.000–1.000)1.000 (1.000–1.000)1.000 (1.000–1.000)1.000 (1.000–1.000)
Age1.097 *** (1.089–1.105)1.104 *** (1.091–1.117)1.091 *** (1.081–1.102)1.097 *** (1.089–1.106)
Age^20.999 *** (0.999–0.999)0.999 *** (0.999–0.999)0.999 *** (0.999–0.999)0.999 *** (0.999–0.999)
Male0.857 *** (0.829–0.885) 0.925 (0.828–1.035)
Marriage Status a
Unmarried0.887 ** (0.797–0.986)0.945 (0.832–1.074)0.788 ** (0.645–0.962)0.887 ** (0.797–0.986)
Co-habitating1.337 *** (1.092–1.637)1.334 *
(0.954–1.867)		1.373 ** (1.072–1.757)1.340 *** (1.095–1.641)
Divorced1.037 (0.924–1.163)1.093 (0.941–1.268)0.952 (0.794–1.141)1.033 (0.921–1.159)
Widow0.946 ** (0.897–0.996)1.046 (0.948–1.153)0.913 *** (0.858–0.971)0.947 ** (0.899–0.998)
Employment Status b
Unemployed1.182 ** (1.003–1.393)1.206 (0.945–1.538)1.161 (0.931–1.448)1.183 ** (1.004–1.394)
Exited Labor Market1.287 *** (1.242–1.333)1.441 *** (1.358–1.531)1.200 *** (1.148–1.253)1.286 *** (1.242–1.332)
Studying1.034 (0.838–1.276)1.087 (0.803–1.469)1.032 (0.756–1.410)1.034 (0.838–1.277)
Education Level c
Elementary0.981 (0.943–1.021)1.009 (0.948–1.075)0.959 (0.911–1.010)0.979 (0.941–1.018)
Junior High0.878 *** (0.840–0.918)0.913 *** (0.854–0.976)0.852 *** (0.802–0.905)0.876 *** (0.838–0.916)
High School/Secondary/Technical/Vocational0.795 *** (0.748–0.845)0.845 *** (0.774–0.921)0.752 *** (0.689–0.821)0.792 *** (0.746–0.842)
Junior College0.745 *** (0.667–0.832)0.804 *** (0.688–0.940)0.690 *** (0.589–0.807)0.741 *** (0.664–0.827)
Bachelor’s Degree and Higher0.726 *** (0.630–0.836)0.883 (0.735–1.060)0.571 *** (0.456–0.716)0.721 *** (0.626–0.831)
Provincial Fixed EffectsYesYesYesYes
Observations30,65715,30515,35230,657
Notes: *** p < 0.01, ** p < 0.05, * p < 0.1. a Control group is married. b Control group is employed. c Control group is illiterate or semi-illiterate.
Table
Table 3. Prevalence of reporting fair and poor health values for the women sample of different age separately.
Table 3. Prevalence of reporting fair and poor health values for the women sample of different age separately.
VariablesPR (95%CI)PR (95%CI)PR (95%CI)
16–4041–60Aged 60 and Older
Constant0.040 *** (0.006–0.255)0.002 *** (0.000–0.033)0.321 (0.025–4.061)
Social Relations
Mobile Phone Bill1.002 (0.991–1.004)1.003 (0.994–1.007)1.003 (0.995–1.008)
Weekly Dinners with Family Members1.029 ** (1.003–1.056)1.006 (0.990–1.021)1.012 (0.998–1.026)
Neighbor Help1.002 (0.894–1.122)0.932 ** (0.877–0.991)0.942 **(0.888–0.999)
Trust
Trust Others0.736 ***(0.658–0.822)0.871 *** (0.822–0.924)0.960 (0.908–1.014)
Subjective Feelings
No Feelings of Loneliness0.572 *** (0.513–0.637)0.770 *** (0.727–0.816)0.771 *** (0.729–0.817)
Attachment Towards Community0.741 *** (0.662–0.830)0.863 *** (0.812–0.918)0.925 ** (0.870–0.985)
Organizational Engagement
Has Religious Faith1.005 (0.946–1.119)1.005 (0.931–1.086)1.006 (0.940–1.077)
Communist Party or Youth League Member0.988 (0.842–1.159)0.971 (0.858–1.099)0.897 * (0.797–1.011)
Household Income(per capita)1.000 (1.000–1.000)1.000 (1.000–1.000)1.000 (1.000–1.000)
Age1.043 (0.938–1.159)1.209 *** (1.092–1.339)1.013 (0.946–1.085)
Age^21.000 (0.998–1.002)0.998 *** (0.997–0.999)1.000 (0.999–1.000)
Marriage Status a
Unmarried0.747 ** (0.577–0.968)1.498 ** (1.018–2.205)0.933 (0.511–1.704)
Co-habitating1.449 (0.691–3.039)1.226 (0.864–1.740)1.511 *** (1.260–1.812)
Divorced0.748 (0.455–1.229)1.002 (0.798–1.260)0.998 (0.700–1.423)
Widow0.895 (0.414–1.935)0.839 ** (0.731–0.962)0.927 ** (0.862–0.997)
Employment Status b
Unemployed0.907 (0.599–1.374)1.200 (0.903–1.595)1.975 *** (1.717–2.273)
Exited Labor Market0.965 (0.840–1.108)1.219 *** (1.140–1.303)1.316 *** (1.233–1.405)
Studying1.077 (0.753–1.540)
Education Level c
Elementary1.002 (0.838–1.198)0.960 (0.891–1.035)0.896 *** (0.825–0.973)
Junior High0.792 ** (0.659–0.952)0.896 *** (0.827–0.970)0.794 *** (0.705–0.895)
High School/Secondary/Technical/Vocational0.672 *** (0.534–0.844)0.761 *** (0.677–0.854)0.856 * (0.723–1.013)
Junior College0.617 *** (0.467–0.815)0.745 ** (0.579–0.957)0.969 (0.693–1.355)
Bachelor’s Degree and Higher0.644 *** (0.471–0.881)0.324 *** (0.170–0.619)0.702 (0.367–1.341)
Provincial Fixed EffectsYesYesYes
Observations610158013450
Notes: *** p < 0.01, ** p < 0.05, * p < 0.1. a Control group is married. b Control group is employed. c Control group is illiterate or semi-illiterate.
Publisher’s Note: MDPI stays neutral with regard to jurisdictional claims in published maps and institutional affiliations.

Share and Cite

MDPI and ACS Style

Gu, J.; Zhu, R. Social Capital and Self-Rated Health: Empirical Evidence from China. Int. J. Environ. Res. Public Health 2020, 17, 9108. https://doi.org/10.3390/ijerph17239108

AMA Style

Gu J, Zhu R. Social Capital and Self-Rated Health: Empirical Evidence from China. International Journal of Environmental Research and Public Health. 2020; 17(23):9108. https://doi.org/10.3390/ijerph17239108

Chicago/Turabian Style

Gu, Jiafeng, and Ruiyu Zhu. 2020. "Social Capital and Self-Rated Health: Empirical Evidence from China" International Journal of Environmental Research and Public Health 17, no. 23: 9108. https://doi.org/10.3390/ijerph17239108

Note that from the first issue of 2016, this journal uses article numbers instead of page numbers. See further details here.

Article Metrics

Back to TopTop