1. Introduction
Self-esteem is an important subject in the field of psychology and social sciences. Most psychologists agree that self-esteem plays an essential role in mental health. In this regard, the literature has shown that lower self-esteem is associated with depression (Cheng & Furnham, 2003; Orth, et al., 2008; Steiger, 2014; Park & Yang,2017), disordered eating (Colmsee, et al., 2021; Jonstang, 2009), internet addiction (Zhou & Wan ,2021; Aydm & San,2011), in addition to other mental health problems (Ybrandt & Armelius, 2010; Merianos et al., 2013). Although research shows the importance of self-esteem, several studies have shown that Asian participants’ scores in self-esteem tests were consistently lower than American and Western participants’ scores. It seems that people in various cultures have different definitions of self-esteem.
Some studies also maintain that the definition of self-esteem can be different in various cultures and situations (Twenge & Crocker, 2002; Bachman & O’Malley, 1984; Feather & McKee, 1993; Hoge & McCarthy, 1984; Luk & Bond, 1992; Trafimow et al., 1991; Verkuyten, 1993; Singelis et al., 1999; Cia et al., 2009; Heine et al., 1999; Kim et al., 2010; Brown et al., 2009). Wang and Ollendick (2001) investigated self-esteem in Chinese and Western children and found that self-esteem does not have the same definition across these collectivist and individualistic cultures. They found that scores on self-esteem scales are lower among Asians because this population does not tend to express positive evaluations about themselves or they describe themselves in relation to others. Also, in these cultures, interpersonal relationships and dependency on the group are encouraged. In this regard, Kitayama et al. (1999) proposed the self-construal theory. According to the self-construal theory, people in different cultures have strikingly different construal of the self, of others, and of interdependence. They believe that many Asian cultures have distinct conceptions of individuality that insist on the fundamental relatedness of individuals to each other. The emphasis is on attending to others, fitting in, and harmonious interdependence. American culture neither assumes nor values such an overt connectedness among individuals. In contrast, individuals seek to maintain their independence from others by attending to the self and by discovering and expressing their unique inner attributes. For example, American situations are relatively conducive to self-enhancement and American people are relatively likely to engage in self-enhancement while Japanese situations are relatively conducive to self-criticism and Japanese people are comparatively likely to engage in self-criticism.
Moreover, the factors that lead people to see themselves positively can be different. As a result, a self-concept instrument should consider multiple dimensions of the self. However, many existing measures of global self-esteem, such as Rosenberg’s Self-esteem Scale (SES) and Coopersmith’s Self-esteem Inventory (SEI) were developed based on Western cultures. Accordingly, we need a scale that considers multiple dimensions of the self and sources of self-esteem in people from various cultures. This issue expresses the need for a new scale that is useful in different cultures. One of the scales that assesses different facets of self-esteem is the Adult Source of Self-esteem Inventory (ASSEI) (Fleming & Elovson, 1989). This scale was designed based on the self-construal theory of Markus and Kitayama (1999) and has a multidimensional structure. The main advantage of the scale is that it assesses multiple dimensions of the self in different cultures. Also, it considers the factors that can affect self-esteem as the source of self-esteem. This is important because self-esteem can be different from one domain to another or different throughout an individual’s life span. Therefore, ASSEI can be used as a self-esteem instrument for various people and in different cultures. Although the scale was investigated in many cultures, ASSEI is not validated in the Persian language. Therefore, this study aims to assess the psychometric properties of the Persian version of Adult Source of Self-esteem Inventory (ASSEI) among Iranian students.

2. Participants and Methods 
Study participants and procedures
The participants were 500 students, namely 350 (70%) females and 150 (30%) males from kharazmi University in Iran. The age range was from 18 to 35 years. The research data were collected from March to June 2018. We used the Persian version of ASSEI by Elovson and Fleming along with SES by Rosenberg. At first, the original version of the questionnaire was translated into Persian by an expert translator using the back translation method. Then, a psychology expert investigated the content. Finally, the scale was distributed among students. The data were gathered through a paper-pencil questionnaire. The average time for answering the questions was 20 min. All students participated voluntarily in the research and the investigator provided the necessary help.
Measures
Adult Sources of Self-Esteem Scale (ASSEI)
The Persian version of Adult Source of Self-esteem Inventory (ASSEI) was used. This scale has two separate form to complete that including: Form A and Form B, form A, asses the importance of aspects and form B, asses satisfaction with aspects, each form containing the 20 items to be rated on a 0-10 scale. participants rate their agreement or disagreement with each option on this rate. Also, this scale has 8 categories, including appearance and popularity, intellect and abilities, personal achievement and recognition, personal control, ethics and integrity, relations with others, and religion or spirituality. ASSEI has been studied in various studies and its validity has been reported as favorable. The validity of the scale was obtained at the range of 0.85 to 0.97 using the Cronbach α method (Watkins & Yu, 1993; Van de Vijver & Watkins, 2006; Li et al., 2006; Marčič & Kobal Grum, 2011). In Iran, this questionnaire has not been used in research yet.
Rosenberg’s Self-Esteem Scale
Rosenberg’s SES was used to assess convergent validity. This scale has 10 items that refer to self-respect and self-acceptance rated on a 4-point Likert-based scale, ranging from 1 (totally disagree) to 4 (totally agree). Items 1, 3, 4, 7, and 10 are positively worded while items 2, 5, 6, 8, and 9 are worded negatively. This scale has been widely used in studies related to self-esteem and its validity and reliability have been reported as favorable (Robins et al., 2001; Martin-Albo et al., 2007; Goldsmith, 1986; Sinclair, 2010; Quilty et al., 2006; Shapurian et al., 1987). In most studies, the internal consistency with the Cronbach α method was shown in the range of 0.80 to 0.89 (Kourakou et al., 2021; Hatcher & Hall, 2009; Piyavhatkul, 2011; Franck et al., 2008). In Iran, some studies reported moderate to satisfactory levels of internal consistency using Cronbach’s alpha and showed that the scale has the unidimensionality factor structure (Mohammadi et al., 2008; Shapurian et al., 1987).

3. Results 
Data analysis
We used the software R (R Core Team, 2019), the psych package (Revelle, 2020), EGAnet (Golino & Christensen, 2020), and lavaan (Rosseel, 2012), along with MPLUS (Muthén & Muthén, 1998-2011) to analyze the data. The methods used for the factor structure investigation included parallel analysis, exploratory graph analysis (EGA), and exploratory factor analysis (EFA). Then the identified factors structures were checked out by confirmatory factor analysis (CFA). Finally, composite reliability and discrimination validity of factors from different models were checked by omega and AVE (average variance extracted) indices. In addition, the ubiquitous α index was used to examine the internal consistency.
Items statistics
According to Table 1 and Figure 1 (for item 5) and Figure 2 (for item 13), not all options discriminate between the traits measured by items. An 11-points Likert scale (0 to 10) was used in the ASSEI test. As the results show, using a wide range is undesirable as it requires increasing the sample size to accurately estimate item parameters. Also, the preference of the person in selecting the items is on the marginal options (that is, options 0, 1, 2, and 10). Other options neither discriminated persons well nor received much attention (Table 1 and item 5 plots, for example). Therefore, appropriate points for items in this scale should be lower than 11. Meanwhile, 7, 5, or even 3 points are a good option for this scale. According to Table 1, items 1 and 6 have the lowest correlation with the total raw score. The mean of all items was greater than 7 and their standard divisions were about 2 for all items, except for item 6 which had the greatest mean and standard deviation.









Parallel analysis and related statistics
The results from parallel analysis by the psych package (Revelle, 2020) indicated 4 factors and 3 components. The Velicer’s MAP (minimum average partial) values for the first 4 factors were 0.024, 0.021, 0.018, and 0.020, respectively; accordingly, this shows 3 factors. The SRMR (standardized root mean square residual) statistic for the first factors were 0.096, 0.063, 0.039, and 0.037, respectively. This again shows that 3 factors are enough for explaining items’ correlations. The lowest BIC (Bayesian Information Criterion) and SABIC (sample-size-adjusted BIC) values (-177.09 and 245.16, respectively) were achieved for 3 factors.
Exploratory graph analysis 
The results from the EGA method (Golino and Christensen, 2020) showed 3 factors. The pattern of items in 3 clusters (factors) can be seen in Figure 3. The fitness of the structures suggested by EGA can be verified using the CFA method and the stability of EGA’s estimation can be investigated via parametric and nonparametric bootstraps, which both are based on random sampling. We used 1000 samples for both of these methods. 



Based on the observed correlation matrix, the parametric bootstrap generated data from a multivariate normal distribution with the same number of cases and variables as the original sample. Then, the computation and analysis of the partial correlation matrix for each sample was done. Finally, a typical median network structure, which is formed by the median or mean pairwise (partial) correlations over n bootstraps (n=1000 in the present research) was graphed. The nonparametric bootstrap resampled from the data sample; therefore, it does not rely on a specific distribution. This approach, however, can be less reliable when outliers exist in the sample which then gets resampled and appears in the sample more often than it would be expected; that is, outliers can have stronger effects on the results than they would otherwise. According to Table 2, while 3 factor is the more dominant structure (66.1%) based on parametric bootstrap, the repetition percentage of 4, 5, and 6 structures are very low. Although 4 factor is the most dominant (46%) for nonparametric bootstrap, the repetition of 3 factor structure is very close to it (43.9%). The repetition of 5, 6, and 7 factor is very low in the nonparametric method, which shows their low stability; therefore, they can be ignored.



Exploratory factor analysis
Exploratory factor analysis results with Geomin (oblique) in Table 3 for 3 and 4 factor structures show that some items have significant loadings on 2 (for example, item 16, 18, and 19 in 3-factor solution) or even 3 factor (for example, item 12 and 13 in 3-factor solutions) structures. Although assigning the items to factors is based on the largest loading, loadings are approximately large for some item crosses. For example, items 18 and 19 in 3-factor solutions load on factors 2 and 3. Accordingly, cross-loadings are less for 4-factor solutions and more for the 3-factor structures.



The pattern of items for various factors (clusters) results from EFA and EGA methods that are shown in Table 4. As shown, a similarity exists between patterns in different methods but the one that has a theoretical interpretation is the EGA results. In addition to the displacement of factors in the results of EGA, EGA parametric bootstrap, and EGA nonparametric bootstrap, the displacement of item 16 between different clusters is the main difference. The results from the EFA method (3 and 4 factors) show that items 10 and 11 constitute the fourth factor (same as the EGA nonparametric bootstrap method). Regardless of factor 4, the first factor for the 3 and 4 factors in EFA is the same and the difference is related to the second and third factors.



Confirmatory factor analysis 
Since all items have 11 choices, we can consider them continuous with non-normal distribution. Accordingly, CFA was done in lavaan (Rosseel, 2012) with weighted least square mean and variance estimation (Li, 2016). According to Table 5, all models fit the data. The model that has the best fitting is related to EGA based on the nonparametric bootstrap method (EGA.NPB) and 4 factors from EFA (EFA4F). However, content investigation of items shows that factors from the EGA method have theoretical justification and interpretation.



In addition to the model’s goodness of fit, other aspects of the models, such as construct reliability and discrimination validity, should be considered for correct score interpretation. Accordingly, the construct reliabilities (composite reliabilities) of factors from different methods along with AVE indices (for discrimination validity) were computed (Table 6). The omega (McDonald, 2013), as a measure of construct reliability, shows a part of the variance of the scale or subscale scores that are explained by a general factor (measured by all items in the scale) or each of the specific factors (measured by some items of the scale). Omega is a model-based reliability method that can be considered an estimation of validity, especially convergent validity.



The problems related to the internal consistency indices, such as α, split-half, and KR20 is that they cannot affect Omega. The α index is a kind of omega if the assumptions of α are to be established (Watkins, 2017). Factors with an omega measure of less than 0.5 should be revised because they are problematic and values equal to or greater than 0.5 are acceptable. Omega values equal to or greater than 0.7 (Hair, Black, Babin & Anderson, 2010) or 0.75 (Reise, 2012) are suitable. While all omega values show convergent validity, AVE indices are below 0.5 for all models. AVE of 0.5 or higher indicates that, on average, the construct explains 50% or more of the variance of its indicators. As Fornell and Larcker (1981) maintained, we can accept 0.4 for AVE because if AVE is less than 0.5 while composite reliability is higher than 0.6, the convergent validity of the construct is still adequate. Accordingly, the AVE for 3 factors from the EGA method is 0.414, 0.352, and 0.470, respectively which show low convergent validity for 2 factor. On the other hand, discriminant validity is present when the shared variance within a construct (AVE) always exceeds the shared variance with all other constructs (Hair, et al., 2019). The squared correlations between factors 1 and 2, 1 and 3, and 2 and 3 are 0.36, 0.55, and 0.28, respectively. This shows that the discriminant validity of factors is not high. For 4 factor structure from the EFA (EFA4F) method, the squared correlations between the factors are 0.23, 0.36, 0.25, 0.50, 0.51, and 0.37 respectively. Their AVE is 0.352, 0.497, 0.414, and 0.734, respectively. This shows that discriminant validity in 4 factors structure is comparatively better than 3 factors structure. 
To investigate convergent validity, the correlation of ASSEI subscales in forms A and B and Rosenberg’s self-esteem are reported in Table 7.



Although no significant correlation exists between ASSEI subscales in forms A and B and Rosenberg’s self-esteem, the correlation of ASSEI subscales in forms A and B is significant and acceptable. Consequently, based on the boxplot results in Figure 4, the distribution of factor scores in 3 factors is the same with negative skewness. Factor 2 has the largest mean and the lowest dispersion. Although the mean of factors 1 and 3 are approximately equal, the dispersion of factor 3 is more than factor 1. 




4. Discussion
The present study aimed to determine different facets of self-esteem in an Iranian sample and to investigate factor analysis of ASSEI. The result of the explanatory analysis has shown that the scale can be 3 or 4 factors in this sample but the 3 factors structure indicated the maximum fitness and justified an interpretation. Based on this analysis, the first factor contained items 1, 2, 3, 4, and 6. The second factor included items 5, 7, 8, 10, 11, and 20. The third factor included items 9, 12, 13, 14, 15, 16, 17, 18, and 19. The first factor related to the outward self, such as appearance and popularity is called the “outer self”. The second factor refers to the relational dimension, such as relationships with family and society members and even the relationship with God that we called the “relational self”. Consequently, the third factor is related to the personal dimension, such as achievement, intelligence, and abilities that we called the “personal self”.
Although the factor structure in the original version is 2 factors, including independent self and interdependent self, Flemind and Olovson (2008) suggested that the number of useful factors is still an open question and the factor structure of the ASSEI in different studies suggests that either 2, or possibly 3 factors may be useful. Meanwhile, when 2 factors are retained, they may be called “independent or individual) self” and “interdependent or relational self”. They believe when a third factor is retained, it consists of items related to concern for the impression that one makes on others (physical appearance and physical abilities, grooming, being liked). These traits might be called the “inner”, “outer”, and “other” aspects of the self as they pertain to the “personal self”, “impression on others”, and “relational self”, respectively.
Considering that sources of self-esteem can be different in different cultures, we explained these factors in the present sample. For example, relationships among family and society members are common in Iran and people define themselves in terms of these relationships. Even it is important that the outer self and the inner self can be influenced. In other words, relational dimensions of self-esteem are substantial for other dimensions of self. Appearance and outer self are important because evaluations of others in social relationships are important. Also, personal achievements can affect these relationships and mutually influence reaching new connections. This explains that relationships are important to self-concept in some Asian cultures. Therefore, it is necessary to pay attention to cultural and individual differences. Recently, research has concentrated more on cross-cultural studies about self-esteem. For example, Lyu et al., (2019) investigated self-esteem among Chines and American students and indicated that American undergraduates had higher self-esteem compared to Chinese undergraduates. Also, Jung and Lee (2009) compared the appearance self-schema, body image, and self-esteem between Korean and American women. They found that Korean women placed greater importance on appearance, were more critical of their bodies, and revealed lower self‐esteem compared to their American peers. Therefore, the research can investigate the reasons for differences that sometime may result from used measures or different definitions of self-concept in Asian cultures. 
Moreover, the internal consistency of factors by using the Cronbach α method was obtained at 0.90. In addition, the convergent validity of the ASSEI with the Rosenberg self-esteem scale was weak. We suppose that the Rosenberg general self-esteem scale has been used to measure global self-esteem while ASSEI is designed to measure various fields of self-esteem. So, it is better to use measures of self-esteem that are multidimensional for convergent validity.

5. Conclusion
Self-esteem has multiple dimensions and it is better to understand all its aspects. Meanwhile, self-esteem can be different in various cultures because people of different cultures define themselves based on values and criteria that their society determines and the importance of each dimension can be different in every society and culture. This creates a need to use new scales that could be useful in various cultures. Based on our results in this research, we conclude that the factors structures of ASSEI as a self-esteem instrument are 3 factors. Accordingly, the outer and relational self can indicate the importance of social dimensions in the Iranian population. The results can be used in clinical situations and social research to assess what leads individuals to see themselves more or less positively in the Iranian population. 

Limitations and future research
The present study faced some limitations. Our sample was from university students and the results cannot be generalized to other Iranian populations, especially considering that there is ethnic diversity in Iran. Also, the number of male participants is less than female participants and all participants were in the age range of 18-35 years. Gender and age can lead to different results on this scale. Although we suggest the scale be used in greater groups that involve different gender and age range along with various ethnicity. 

Ethical Considerations

Compliance with ethical guidelines
This research adheres to all applicable standards regarding survey research ethics throughout the data collection, data analysis, and reporting processes.

Funding
The study was carried out with the personal support of the corresponding author.

Authors' contributions
Conceptualization and Supervision: Negar Sadeghi; Methodology: Balal Izanlu; Investigation, Writing–original draft: Negar Sadeghi; Writing--review & editing: Negar Sadeghi, Balal Izanlu; Data collection: Negar Sadeghi; Data analysis: Balal Izanlu.

Conflict of interest
The authors declare no conflict of interest.

Acknowledgments
Thanks to students for the contribution in this study.



References
Aydm, B., & San, S. V. (2011). Internet addiction among adolescents: The role of self-esteem. Procedia-Social and Behavioral Sciences, 15, 3500-3505. [DOI:10.1016/j.sbspro.2011.04.325]
Bachman, J. G., & O’Malley, P. M. (1984). Black-white differences in self-esteem: Are they affected by response styles? American Journal of Sociology, 90(3), 624-639. [DOI:10.1086/228120]
Brown, J. D., Cai, H., Oakes, M. A., & Deng, C. (2009). Cultural similarities in self-esteem functioning: East is east and west is west, but sometimes the twain do meet. Journal of Cross-Cultural Psychology, 40(1), 140-157. [DOI:10.1177/0022022108326280]
Cai, H., Wu, Q., & Brown, J. D. (2009). Is self‐esteem a universal need? Evidence from The People’s Republic of China. Asian Journal of Social Psychology, 12(2), 104-120. [DOI:10.1111/j.1467-839X.2009.01278.x]
Cheng, H., & Furnham, A. (2003). Personality, self-esteem, and demographic predictions of happiness and depression. Personality and Individual Differences, 34(6), 921-942. [DOI:10.1016/S0191-8869(02)00078-8]
Colmsee, I. S. O., Hank, P., & Bošnjak, M. (2021). Low Self-esteem as a risk factor for eating disorders. Zeitschrift für Psychologie, 229(1),48-69. [DOI:10.1027/2151-2604/a000433]
Feather, N. T., & McKee, I. R. (1993). Global self-esteem and attitudes toward the high achiever for Australian and Japanese students. Social Psychology Quarterly, 56(1), 65-76. [DOI:10.2307/2786646]
Fleming, J. S., & Elovson, A. (2008). The Adult Sources of Self-Esteem Scale (ASSEI): Development, rationale and history. Arizona: Prescott. [Link]
Fornell, C., & Larcker, D. F. (1981). Evaluating structural equation models with unobservable variables and measurement error. Journal of Marketing Research, 18(1), 39–50. [DOI:10.1177/002224378101800104]
Franck, E., De Raedt, R., Barbez, C., & Rosseel, Y. (2008). Psychometric properties of the Dutch Rosenberg self-esteem scale. Psychologica Belgica, 48(1), 25-35. [Link]
Golino, H., & Christensen, A. P. (2020). EGAnet: Exploratory Graph Analysis -- A framework for estimating the number of dimensions in multivariate data using network psychometrics. Retrived from: [Link]
Hatcher, J., & Hall, L. A. (2009). Psychometric properties of the Rosenberg self-esteem scale in African American single mothers. Issues in Mental Health Nursing, 30(2), 70-77. [PMID]
Hair, J. F., Black, W. C., Babin, B. J., Anderson, R. E., & Tatham, R. L. (2010). Multivariate data analysis. Upper Saddle River: Pearson Prentice Hall. [Link]
Heine, S. J., Lehman, D. R., Markus, H. R., & Kitayama, S. (1999). Is there a universal need for positive self-regard? Psychological Review, 106(4), 766-794. [DOI:10.1037/0033-295X.106.4.766] [PMID]
Hoge, D. R., & McCarthy, J. D. (1984). Influence of individual and group identity salience in the global self-esteem of youth. Journal of Personality and Social Psychology, 47(2), 403-414. [PMID]
Jonstang, I. C. (2009). The effect of body dissatisfaction on eating disorder symptomatology: mediating effects of depression and low self-esteem: A partial test of the Dual-Pathway Model [MSc. thesis]. Oslo: University of Oslo. [Link]
Jung, J., & Lee, S. H. (2006). Cross‐cultural comparisons of appearance self‐schema, body image, self‐esteem, and dieting behavior between Korean and US women. Family and Consumer Sciences Research Journal, 34(4),350-365. [DOI:10.1177/1077727X06286419]
Kourakou, A., Tigani, X., Bacopoulou, F., Vlachakis, D., Papakonstantinou, E., & Simidala, S., et al. (2021). The Rosenberg Self-Esteem Scale: Translation and validation in the Greek language in adolescents. Advances in Experimental Medicine and Biology, 1339, 97–103. [PMID]
Kim, Y. H., Chiu, C. Y., Peng, S., Cai, H., & Tov, W. (2010). Explaining East-West differences in the likelihood of making favorable self-evaluations: The role of evaluation apprehension and directness of expression. Journal of Cross-Cultural Psychology, 41(1), 62-75. [DOI:10.1177/0022022109348921]
Kitayama, S., Markus, H. R., Matsumoto, H., & Norasakkunkit, V. (1997). Individual and collective processes in the construction of the self: Self-enhancement in the United States and self-criticism in Japan. Journal of Personality and Social Psychology, 72(6), 1245-1267. [DOI:10.1037/0022-3514.72.6.1245] [PMID]
Orth, U., Robins, R. W., & Roberts, B. W. (2008). Low self-esteem prospectively predicts depression in adolescence and young adulthood. Journal of Personality and Social Psychology, 95(3), 695-708. [PMID]
Piyavhatkul, N., Aroonpongpaisal, S., Patjanasoontorn, N., Rongbutsri, S., Maneeganondh, S., & Pimpanit, W. (2011). Validity and reliability of the Rosenberg Self-Esteem Scale-Thai version as compared to the Self-Esteem Visual Analog Scale. Journal of the Medical Association of Thailand, 94(7), 857-862. [PMID]
Park, K., & Yang, T. C. (2017). The long-term effects of self-esteem on depression: The roles of alcohol and substance use during young adulthood. The Sociological Quarterly, 58(3), 429-446. [DOI:10.1080/00380253.2017.1331718] [PMID] [PMCID]
Li, C. H. (2016). The performance of ML, DWLS, and ULS estimation with robust corrections in structural equation models with ordinal variables. Psychological Methods, 21(3), 369-387. [DOI:10.1037/met0000093] [PMID]
Li, E. P., Tam, A. S., & Man, D. W. (2006). Exploring the self-concepts of persons with intellectual disabilities. Journal of Intellectual Disabilities, 10(1), 19-34. [DOI:10.1177/1744629506062270] [PMID]
Luk, C. L., & Bond, M. H. (1992). Explaining Chinese self-esteem in terms of the self-concept. Psychologia: An International Journal of Psychology in the Orient, 35(3), 147–154. [PMID]
Lyu, H., Du, G., & Rios, K. (2019). The relationship between future time perspective and self-esteem: A cross-cultural study of Chinese and American college students. Frontiers in Psychology, 10, 1518. [DOI:10.3389/fpsyg.2019.01518] [PMID] [PMCID]
Marcic, R., & Grum, D. K. (2011). Gender differences in self-concept and self-esteem components. Studia Psychologica, 53(4), 373-384. [Link]
Markus, H. R., & Kitayama, S. (1991). Culture and the self: Implications for cognition, emotion, and motivation. Psychological Review, 98(2), 224-253. [DOI:10.1037/0033-295X.98.2.224]
Martin-Albo, J., Núñez, J. L., Navarro, J. G., & Grijalvo, F. (2007). The Rosenberg Self-Esteem Scale: Translation and validation in university students. The Spanish Journal of Psychology, 10(2), 458-467. [DOI:10.1017/S1138741600006727] [PMID]
McDonald, R. P. (2013). Test theory: A unified treatment. New York: Psychology Press. [DOI:10.4324/9781410601087]
Merianos, A. L., Nabors, L. A., Vidourek, R. A., & King, K. A. (2013). The impact of self-esteem and social support on college students’mental health. American Journal of Health Studies, 28(1), 27-34. [Link]
Muthén, L. K., & Muthén, B. O. (1998). Mplus user’s guide. Los Angeles (CA): Muthén & Muthén. [Link]
Goldsmith, R. E. (1986). Dimensionality of the Rosenberg Self-Esteem Scale. Journal of social Behavior and Personality, 1(2), 253-264. [Link]
Quilty, L. C., Oakman, J. M., & Risko, E. (2006). Correlates of the Rosenberg self-esteem scale method effects. Structural Equation Modeling, 13(1), 99-117. [DOI:10.1207/s15328007sem1301_5]
Team, R. C. (2019). R: A language and environment for statistical computing. R foundation for statistical computing. Vienna: Austria. [Link]
Reise, S. P. (2012). Invited Paper: The rediscovery of bifactor measurement models. Multivariate Behavioral Research, 47(5), 667–696. [PMID] [PMCID]
Revelle, W. R. (2020). Psych: Procedures for personality and psychological research. Illinois: Northwestern University. [Link]
Robins, R. W., Hendin, H. M., & Trzesniewski, K. H. (2001). Measuring global self-esteem: Construct validation of a single-item measure and the Rosenberg Self-Esteem Scale. Personality and Social Psychology Bulletin, 27(2), 151-161. [DOI:10.1177/0146167201272002]
Rosseel, Y. (2012). lavaan: An R package for structural equation modeling. Journal of Statistical Software, 48(2), 1-36. [DOI:10.18637/jss.v048.i02]
Shapurian, R., Hojat, M., & Nayerahmadi, H. (1987). Psychometric characteristics and dimensionality of a Persian version of Rosenberg Self-esteem Scale. Perceptual and Motor Skills, 65(1), 27-34. [DOI:10.2466/pms.1987.65.1.27] [PMID]
Schwartz, S. H. (1992). Universals in the content and structure of values: Theoretical advances and empirical tests in 20 countries. Advances in Experimental Social Psychology, 25, 1-65. [DOI:10.1016/S0065-2601(08)60281-6]
Sinclair, S. J., Blais, M. A., Gansler, D. A., Sandberg, E., Bistis, K., & LoCicero, A. (2010). Psychometric properties of the Rosenberg Self-Esteem Scale: Overall and across demographic groups living within the United States. Evaluation & The Health Professions, 33(1), 56-80. [DOI:10.1177/0163278709356187] [PMID]
Singelis, T. M., Bond, M. H., Sharkey, W. F., & Lai, C. S. Y. (1999). Unpackaging culture’s influence on self-esteem and embarrassability: The role of self-construals. Journal of Cross-Cultural Psychology, 30(3), 315-341. [DOI:10.1177/0022022199030003003]
Steiger, A. E., Allemand, M., Robins, R. W., & Fend, H. A. (2014). Low and decreasing self-esteem during adolescence predict adult depression two decades later. Journal of Personality and Social Psychology, 106(2), 325-338. [PMID]
Twenge, J. M., & Crocker, J. (2002). Race and self-esteem: Meta-analyses comparing whites, blacks, Hispanics, Asians, and American Indians and comment on Gray-Little and Hafdahl (2000). Psychological Bulletin, 128(3), 371–420. [DOI:10.1037/0033-2909.128.3.371] [PMID]
Trafimow, D., Triandis, H. C., & Goto, S. G. (1991). Some tests of the distinction between the private self and the collective self. Journal of Personality and Social Psychology, 60(5), 649–655. [DOI:10.1037/0022-3514.60.5.649]
Van de Vijver, F. J., & Watkins, D. (2006). Assessing similarity of meaning at the individual and country level. European Journal of Psychological Assessment, 22(2), 69-77. [DOI:10.1027/1015-5759.22.2.69]
Verkuyten, M. (1993). Self-esteem among ethnic minorities and three principles of self-esteem formation: Turkish children in the Netherlands. International Journal of Psychology, 28(3), 307-321. [Link]
Wang, Y., & Ollendick, T. H. (2001). A cross-cultural and developmental analysis of self-esteem in Chinese and Western children. Clinical Child and Family Psychology Review, 4(3), 253-271. [Link]
Watkins, M. W. (2017). The reliability of multidimensional neuropsychological measures: From alpha to omega. The Clinical Neuropsychologist, 31(6-7), 1113-1126. [Link]
Watkins, D., & Yu, J. (1993). Gender differences in the source and level of self-esteem of Chinese college students. The Journal of social psychology, 133(3), 347–352. [PMID]
Ybrandt, H., & Armelius, K. (2010). Peer aggression and mental health problems: Self-esteem as a mediator. School Psychology International, 31(2), 146-163. [Link]
Zhou, G., & Wang, E. (2021). Effects of self-concealment and self-esteem on Internet addiction in college students. Social Behavior and Personality: An International Journal, 49(7), 1-9. [DOI:10.2224/sbp.10370]