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Catalan and Hungarian validation of the Zuckerman-Kuhlman-Aluja personality questionnaire (ZKA-PQ).

Zuckerman, Kuhlman, Joireman, Teta, and Kraft (1993) have proposed an alternative five-factor model (AFFM) that includes only dimensions with a substantial biological-evolutionary basis. This model is an extension of the Zuckerman's Sensation Seeking personality theory (Aluja & Garcia, 2005; Rosenblitt, Soler, Johnson, & Quadagno, 2001). The basic traits in the AFFM measured by the Zuckerman-Kuhlman Personality Questionnaire (ZKPQ) are: Neuroticism-Anxiety (N-Anx), Activity (Act), Sociability (Sy), Impulsive Sensation Seeking (ImpSS) and Aggression-Hostility (Agg-Host). The ZKPQ is available for adults and also for children populations (Aluja, Balleste, & Torrubia, 1999; Aluja, Garcia, & Garcia, 2004). A full description and psychometric properties of the questionnaire can be found in works of Zuckerman (2002, 2008) and Joireman and Kuhlman (2004).

The ZKPQ (and its shortened version ZKPQ-50-CC) has turned out to have a robust factor structure and acceptable psychometric properties in various countries (Aluja et al,, 2006), which can be explained by a strong psychobiological basis. The original version of the ZKPQ has been adapted in different countries and languages: China (Wu et al., 2000), Germany (Ostendorf & Angleitner, 1994), Italy (De Pascalis & Russo, 2003), Japan (Shiomi et al., 1996), and Spain (Catalan [Goma-i-Freixanet, Valero, Punti, & Zuckerman, 2004; Goma-i-Freixanet, Wismeijer, & Valero, 2005], and Spanish versions [Aluja et al., 2002, 2004; Herrero, Vina, Gonzalez, Ibanez, & Penate, 2001; Romero, Luengo, Gomez-Fraguela, & Sobral, 2002]). The cross-cultural shortened form (ZKPQ-50-CC) was also developed in English, French, German, and Spanish languages by Aluja et al. (2006).

The ZKA-PQ was developed starting with a pool of 537 items, but the final version contained only 200 items, 10 items per facet. Items representing behaviors, intentions and attitudes were written for each proposed facet by relying on the current literature, and adopting the classic rational-empirical approach. The item content was related to the respective theoretical constructs. There were 20 items designed for each facet and 100 for each factor, which included several items from the original ZKPQ. Additionally, permissions were obtained to include: a) 29 items from the Buss and Perry (1992) Questionnaire of Aggressiveness (AG) in the Aggressiveness-hostility dimension; and b) 37 items from the UPPS Impulsive Behavior Scale (Lynam, Smith, Whiteside, & Cyders, 2006). According to Zuckerman (2005), the different types of impulsivity may be related to different basic personality factors, thus it was considered to be important to include more impulsivity scales. The AG and UPPS items were translated several times from English to Spanish and vice-versa during the back-translation process. A series of factor analyses have yielded 10 items per each of the 20 facets. The final structure was tested in two different Spanish samples (calibration and validation) and in an American sample (Aluja et al., 2010). The ZKA-PQ has a Likert-type 4-point response scale, which can also improve psychometric properties (see Muniz, Garcia-Cueto, & Lozano, 2005) and increase effect sizes (Johnson, Krueger, Bouchard, & McGue, 2002). There have also been changes in the names of the original ZKPQ factors: AG: Aggression, AC: Activity, EX: Extraversion, NE: Neuroticism, SS: Sensation Seeking (Aluja et al., 2010).

ZKA-PQ was developed within Spanish and American samples and was also validated in four French speaking countries (Aluja et al., 2010; Rossier, Hansenne, Baudin, & Morizot, 2012). Exploratory factor analyses and Cronbach alpha reliability analyses have shown that the structural replicability is very high, both for the dimensions and facet scales. However, confirmatory factor analyses--probably due to some covariance between facets and other factors--yielded unsatisfactory fit indices. In American and Spanish samples, the hostility (AG4) and the positive emotion (EX1) facets loaded also on the neuroticism factor and the exhibitionism (EX3) and work energy (AC4) facets had high secondary loadings on the SS factor (Aluja et al., 2010). In French speaking samples, restlessness (AC3) loaded also on aggression and positive emotions (EX1) on neuroticism.

The respondents differed in language and culture. The Catalan language is of a Latin origin and is used by seven million people in Spain. It is also spoken in Valencian country, the Balearic Islands (Spain), Andorra, in five regions of France, and in Alghero (city of Sardinia).

Hungarian is an Uralic language, part of the Ugric group of languages. It is the official language in Hungary but it is also spoken by Hungarian communities in the seven neighboring countries. Altogether, there are 14-15 million Hungarian-speaking individuals.

In such cross-cultural setting, the overarching goal of this study was to assess the reliability and cross-cultural validity of Catalan and Hungarian versions of the ZKA-PQ. As our main goal was to test structural invariance of the new facet-version questionnaire (ZKA-PQ) of the psychobiological alternative five factor personality model, we used online versions to provide a cost-effective and fast access to validate psychometric properties.

Moreover, a secondary benefit was the possibility to test whether significant differences arise between the mean personality profiles in the two different cultural settings.



The Catalan version of the ZKA-PQ was completed by 1,564 subjects, and the Hungarian version was completed by 1,647 subjects. Means and standard deviations for age can be found in Table 1. In both samples, males were significantly older.

T-tests indicated significant gender differences in age with medium effect size in Catalan sample (t = 6.35; p < .001, d = 0.35), and with small effect size in Hungarian sample (t = 2.25, p < .08, d = 0.17). The mean age also differed significantly between the two countries (t = 15.67; p < .001), with a medium effect size (d = 0.56).


The original ZKA-PQ was developed and validated simultaneously in English and Spanish (Castilian) by Aluja et al. (2010). This instrument contains five factors with four facets per factor: Each facet is composed of ten items, making it a 200-item instrument with a 4-point Likert-type response format. Alpha reliabilities were acceptable for both facets and factors in both versions of the instrument (Aluja et al., 2010). The ZKA-PQ was translated from Spanish to Catalan language by Anton Aluja, co-author of the original ZKA-PQ (Aluja et al., 2010) and a bilingual Catalan-Spanish speaker. The ZKA-PQ Hungarian version was translated from English to Hungarian by the first author of this study. It was also translated back to English by a bilingual professional translator and revised by Marvin Zuckerman. After several corrections, the Hungarian ZKA-PQ version was considered appropriate and equivalent in both languages.


Both Catalan and Hungarian respondents of the ZKA-PQ completed an on-line anonymous questionnaire. Catalan participants were recruited through several Catalan universities' mailing lists. Therefore, responses were mainly obtained from people at the university community: students (70%), and teaching and administrative staff (30%). To stimulate participation, an automatically generated interpretative report was provided to all respondents after they had filled out the questionnaire. Hungarian data collection was completed in 19 different companies from 6 different Hungarian cities. These companies all had their own Human Resources Department that helped organize data collection. In return, executives were offered a report on the companies' mean personality profiles.

Data analysis

Descriptive statistics mean differences, alpha internal consistencies for both languages were analyzed. Effect sizes were indicated by Cohen's d values. ANOVA was performed in order to assess differences in facet score means between the two countries. The factor structure in both samples was analyzed through a Principal Axis Factoring (PAF) with Varimax rotation. Additionally, these factor structures were compared and the Tucker's (1951) congruence coefficients were estimated for all of the ZKA-PQ facets. A series of consecutive Confirmatory Factor Analyses (CFA) were carried out, comparing the models with increasing complexity in both cultural settings. First, simple structure was tested (see Figure 1), and then the secondary loadings (salient and modest loadings) were also incorporated.


Descriptive, alpha internal consistencies and mean comparisons between countries

The mean, standard deviation, kurtosis, and skewness values, as well as the Cohen's d values and Cronbach alphas for each of the ZKA-PQ 20 facets and five factors are shown in Table 2.

Reliabilities of most of the facets were adequate in both samples. Several facets had alpha coefficients below .70. AC3 and SS4 had .67 and .65 values in the Catalan sample, while AC1, AC3, NE3 and SS2 had .67, .50, .69 and .61 in the Hungarian sample, respectively. The mean age was significantly higher in the Hungarian sample (d = -.60), but no significant differences were found between factors of the ZKA-PQ, except for NE. The NE means score was lower in the Hungarian sample (d = .87). Country differences in facet mean scores have yielded large effect size (d values exceeding .80) only in the case of NE1 (d = 1.13). Further, medium effect size differences with d values higher than .50 were found in the case of 7 facets (AG1, AG4, AC3, AC4, NE2, NE3, NE4).

To study the potential country differences between the Catalan and Hungarian samples, five ANOVAS (one for each ZKPQ dimension) were conducted with country as the independent and age and sex as the covariate variables. Mean difference in EX was non-significant [F(1, 3189) = .58, p < .447, [[eta].sup.2] = .001], and partial eta squared values indicated negligible effect size for AG ([[eta].sup.2] = .005), AC ([[eta].sup.2] = .007) and SS ([[eta].sup.2] = .006) factors. The age and sex covariates explained between only 1 % and 3.6 % of the variance in these factors. On the other hand, there was a significant country difference in the NE factor. Altogether, country, sex and age explained 18.6 % of Neuroticism variance (adjusted R squared = .186). Country differences had only medium effect size [F(1, 3188) = 292, p < .001, [[eta].sup.2] = .084 (2)], and there was a significant but negligible effect of age [F(1, 3188) = 29.96, p < .001, [[eta].sup.2] = .009] and sex [F(1, 3188) = 74.66, p < .001, [[eta].sup.2] = 023] arose. Interaction effects for 'country x age x sex' resulted in a negligible effect size for all 5 factors ([[eta].sup.2] = 01, 01, 02, 00 and 00 for NE, AC, SS, AG and EX, respectively).

Structure and congruence coefficients by country

Table 2 shows Principal Axis analyses with a varimax rotation of the 20 ZKA-PQ facets. In the Catalan sample, the Kaiser-Meyer-Olkin measures of sample adequacy were above .83. There were two secondary loadings above .40 in the Neuroticism dimension: Hostility (AG4; .47) and Positive Emotions (EX1; -.50). The Catalan version indicated a stable five-factor structure in accordance with the eigenvalue > 1, scree test, and Velicer's MAP methods. The Velicer's minimum average partial (MAP) test compares the relative amount of systematic and unsystematic variance remaining in a correlation matrix after the extraction of an increasing number of components (O'Connor, 2000). The smallest average squared correlation indicates the appropriate number of components. The smallest average squared partial correlation was 025, which supported the extraction of 5 factors. The Tucker's (1951) congruence coefficients after procrustes Varimax rotation were analyzed and the global coefficients were equal or above 97, indicating that the factorial solutions were very similar (see Table 3).

The factorial structures of the Catalan and Hungarian ZKA-PQ were equivalent, only General Activity (AC2: .89) obtained a congruency coefficient below .90.

The same factorial procedure was conducted with the Hungarian ZKA-PQ version. The Kaiser-Meyer-Olkin measures of sample adequacy were above .88. Factors were ordered to coincide with the Catalan factor order. Similarly to the ZKA-PQ Catalan structure, two secondary loadings were above .40 in the Neuroticism dimension: Hostility (AG4 = .53) and Positive Emotions (EX1 = -.46). The smallest average squared partial correlation was .023, supporting the extraction of 5 factors.

Confirmatory factorial analyses

The Confirmatory Factor Analyses (CFA) of the 20 ZKA-PQ facets were based on five latent variables, utilizing the Maximum Likelihood estimation method. Different models of growing complexity were designed: first the simple structure was tested, and then the model was modified to include the relations reflected by the secondary loadings as well (McCrae, Zonderman, Costa, Bond, & Paunonen, 1996). Thus, three different models were constructed in each culture: 1) Simple structure: All facets were linked to their own single latent factor only; 2) Salient loadings: All loadings larger than [+ or -] .30 were built into the model; and 3) Modest loadings: All loadings larger than [+ or -] .15 were built into the model. The parameters were freely estimated in all CFA analyses and the regression coefficients of the error terms over the observed endogenous variables (the facets) were fixed to 1. The model-fit criteria were: The Tucker-Lewis index (TLI) (Bentler & Bonett, 1980; Tucker & Lewis, 1973), the comparative fit index (CFI) (Bentler, 1980), and the root mean square error of approximation (RMSEA, Bollen & Long, 1993; Steiger, 1990). Table 4 shows the results for the four oblique models that were analyzed simultaneously in the two samples with increasing complexity.

These analyses were equivalent to those reported by Aluja et al. (2006), McCrae et al. (1996) on the NEO-PI-R data, and Aluja et al. (2010) on ZKA-PQ data of the original study carried out on Spanish and English samples. All the fit indexes were unsatisfactory. Only the modest loading models that included covariance--based on the three largest modification indices (MI's)--between errors of facets exhibited minimum satisfactory indexes. Nevertheless, when models were built separately for each of the five factors, the fit indices for each ZKA-PQ factor were satisfactory (AGFI and TLI > .90), although unsatisfactory TLI of AC was present in the Catalan sample.


The results of this study indicated that the ZKA-PQ, using different methods of factor extraction, has a stable structure comprising five factors in both Catalan and Hungarian cultures. Reliabilities were acceptable and also similar in both cultures. Procrustes rotations require a linguistic and cultural context as reference a structure. Tucker's congruence coefficient has been used for studying the replicability, with analyses carried out independently for each of the factors (Rolland, 2002). The factorial congruence analyses between the Catalan and Hungarian samples demonstrate a strong factorial equivalence, indicating negligible cultural differences in the structure of the ZKA-PQ in both cross-cultural and linguistic contexts.

The simple structure of the ZKA-PQ was analyzed by Confirmatory Factor Analysis in both samples. Similar results were found in both cultures. The results showed discordance between the outcomes from the EFA and CFA. The robust structure obtained with EFA had poor fit indices in the subsequent CFA. It was necessary to include salient and modest loadings to improve upon the model. It is well known that secondary loadings and correlated items or facets affect the goodness-of-fit indices (Aluja et al., 2010). Only the model that incorporated the modest loadings and the three pairs of correlated facets obtained the minimum satisfactory fit values. All this supports the need of further testing the interactions of facets and factors. A holistic view considers factors as not totally independent dimensions, but as interacting parts of a complex psycho-social-biological system. Further person-oriented analyses can unfold holistic patterns that could help us understand interactions between the different facets and between the different factors along incorporating genetical-environmental interactions.

The main cultural differences that were observed relate to the Neuroticism factor. Lower Neuroticism scores were present in the Hungarian sample. Surprisingly, these scores were slightly affected by age and gender. Assuming that Catalan and Spanish people are culturally more similar than Hungarians and Catalan people, our results are contradictors to previous cross-cultural findings Hungarians scored higher than Spanish participants on the NEO-PI-R (McCrae, 2002) and on the Eysenck Personality Questionnaire (EPQ) Neuroticism factor (Van Hemert, Van de Vijver, Poortinga, & Georgas, 2002) or Sensitivity to Punishment (Caseras et al., 2006). It is important to emphasize that we cannot conclude that the differences between our samples were due cultural differences, as sampling differed in the two countries by more aspects. Thus further studied are needed to test systematically cultural differences in personality profiles.

Moreover, McCrae and Allik (2002) have stated that one should be cautious in interpreting mean personality profiles as 'national types'. There is no strong evidence that mean profiles are in congruence with national stereotypes (McCrae, 2001). Indeed, a study with national character ratings from 49 cultures showed that these did not converge with personality test mean scores (Terracciano et al., 2005). Thus, studying 'national characters' should include more detailed profile analyses, such as the above mentioned holistic-interactionist person-oriented analyses (such as latent class analyses, configuration analyses).

The gender differences were congruent with results of the original validation study (Aluja et al., 2010). Males scored higher than females in Sensation Seeking Factor, also in line with the results of Rossier et al. (2012), as well as the results of numerous studies using different measures of sensation seeking traits (Roberti, 2004). Hungarian males scored higher than females in Aggressiveness factor, but this difference was not found in the Catalan sample. Females scored higher than males in Neuroticism and Activity factors in both samples, and Catalan women were more Extraverted than males.

Further, there are some limitations to this study that need to be mentioned. Although we used two large samples in both countries, there were significant differences in age and social status of the participants. While the Catalan sample consisted of university students and staff members, the Hungarians were individuals employed at different companies from various cities.

The contexts, in which the participation has taken place, were also different in the two samples. The Catalans responded to a collective e-mail that asked to participate for academic purposes, whereas the Hungarians were asked to fill out several questionnaires in order to help make certain changes to the company based on their needs. Therefore, some differences in self-presentation might have arisen. It is possible that all the cultural differences in means can be attributed to the specific situation in which the Hungarians responded to the ZKA-PQ, as they might have been motivated for a more positive self-presentation. This would be in accordance with findings suggesting that employees usually tend to exhibit reduced scores on anxiety-related scales (Daly, Richmond, & Leth, 1979), even when the whole procedure is anonymous. Based on this, we suggest that (1) difference in Neuroticism between the two cultures should be further studied by collecting more representative samples; (2) future studies carried out with the ZKA-PQ in work-related contexts should include social desirability scales.

In summary, the main findings of this study indicate the cross-cultural validity of the Catalan and Hungarian versions of the ZKA-PQ. The ZKA-PQ had good psychometric properties with regard to equivalent factorial structures and similar internal consistencies. Significant differences between countries were found only in Neuroticism dimension, and these differences were only slightly affected by age and gender. These findings, as well as some study limitations, should be replicated and addressed in futures research on the ZKA-PQ.


Received 1 October 2012; Revised 7 March 2013; Accepted 12 July 2013


Aluja A., Balleste J., & Torrubia R. (1999). Self-reported personality and school achievement as predictors of teachers' perceptions of their students'. Personality and Individual Differences, 27, 743-753. 10.1016/S0191-8869(98)00276-1

Aluja A., & Garcia L. F. (2005). Sensation seeking, sexual curiosity and testosterone in inmates. Neuropsychobiology. 51, 28-33. 10.1159/000082852

Aluja A., Garcia O., & Garcia L. F. (2002). A comparative study of Zuckerman's three structural models for personality through the NEO-PI-R, ZKPQ-III-R, EPQ-RS and Goldberg's 50-bipolar adjectives. Personality and Individual Differences, 33, 713-725. 10.1016/S0191-8869(01)00186-6

Aluja A., Garcia O., & Garcia L. F. (2004). Replicability of the three, four and five Zuckerman's personality superfactors: Exploratory and confirmatory factor analysis of the EPQ-RS, ZKPQ and NEO-PI-R. Personality and Individual Differences, 36, 1093-1108.

Aluja A., Kuhlman M., & Zuckerman M. (2010). Development of the Zuckerman-Kuhlman-Aluja Personality Questionnaire (ZKA-PQ): A factor/facet version of the Zuckerma-nKuhlman Personality Questionnaire (ZKPQ). Journal of Personality Assessment, 92, 416-431. 10.1080/00223891.2010.497406

Aluja A., Rossier J., Garcia L. F., Angleitner A., Kuhlman M., & Zuckerman M. (2006). A cross-cultural shortened form of the ZKPQ (ZKPQ-50-CC) adapted to English, French, German, and Spanish languages. Personality and Individual Differences, 41, 619-628. 10.1016/j.paid.2006.03.001

Bentler P. M. (1980). Multivariate analysis with latent variables: Causal modeling. Annual Review of Psychology, 31, 419-456. ps.31.020180.002223

Bentler P. M., & Bonett D. G. (1980) Significance tests and goodness of fit in the analysis of covariance structures. Psychological Bulletin, 88, 588-606. 10.1037/0033-2909.88.3.588

Bollen K. A., & Long J. S. (1993). Testing structural equation models. New York, NY: Sage.

Buss A. H., & Perry M. (1992). The aggression questionnaire. Journal of Personality and Social Psychology, 63, 452-459.

Cohen J. (1988). Statistical power analysis for the behavioral sciences. Hillsdale, NJ: Erlbaum.

Caseras F. X., Fullana M. A., Riba J., Barbanoj M. J., Aluja A., & Torrubia R. (2006). Influence of individual differences in the Behavioral Inhibition System and stimulus content (fear vs. blood-disgust) on affective startle reflex modulation. Biological Psychology, 72, 251-256.

Daly J. A., Richmond V. P., & Leth S. (1979). Social communicate anxiety and the personnel selection process. Testing the similarity effect in selection decisions. Human Communication Research, 6, 18-32. 10.1111/j.1468-2958.1979.tb00288.x

De Pascalis V., & Russo P. M. (2003). Zuckerman-Kuhlman Personality Questionnaire: Preliminary results of the Italian version. Psychological Reports, 92, 965-974.

Goma-i-Freixanet M., Wismeijer A. J., & Valero S. (2005). Consensual validity of the Zuckerman-Kuhlman personality questionnaire: Evidence from self-reports and spouse reports. Journal of Personality Assessment, 84, 279-286.

Goma-i-Freixanet M., Valero S., Punti J., & Zuckerman M. (2004). Psychometric Properties of the Zuckerman-Kuhlman Personality Questionnaire in a Spanish Sample. European Journal of Psychological Assessment, 20, 134-146.

Herrero M., Vina C., Gonzalez M., Ibanez I., & Penate W. (2001). El cuestionario de Personalidad Zuckerman-Kuhlman-III (ZKPQ-III): Version espanola [The Zuckeerman-Kuhlman-III Personality Questionnaire (ZKPQ-III)]. Revista Latinoamericana de Psicologia, 33, 269-287.

Johnson W., Krueger R. F., Bouchard T. J., & McGue M. (2002). The personality of twins: Just ordinary folks. Twin Research, 5, 125-131.

Joireman J., & Kuhlman D. M. (2004). The Zuckerman-Kuhlman Personality Questionnaire: Origin, development, and validity of a measure to assess an alternative Five-Factor Model of personality. In R. M. Stelmack (Ed.), On the psychobiology of personality: Essays in honor of Marvin Zuckerman (pp. 49-64). New York, NY: Elsevier Science.

Lynam D. R., Smith G. T., Whiteside S. P., & Cyders M. A. (2006). The UPPS-P: Assessing five personality pathways to impulsive behavior (Technical Report). West Lafayette, IN: Purdue University.

McCrae R. R. (2001). Trait psychology and culture: Exploring intercultural comparisons. Journal of Personality, 69, 819-846.

McCrae R. R. (2002). NEO-PI-R data from 36 cultures. In R. R. McCrae & J. Allik (Eds.), The five-factor model of personality across cultures (pp. 105-125). New York, NY: Kluwer Academic Publishers. 10.1007/978-1-4615-0763-5

McCrae R. R., & Allik J. (2002). The five-factor model of personality across cultures. (Eds.), New York, NY: Kluwer Academic Publisher.

McCrae R. R., Zonderman A. B., Costa P. T., Bond M. H., & Paunonen S. V. (1996). Evaluating replicability of factors in the revised NEO personality inventory: Confirmatory factor analysis versus procrustes rotation. Journal of Personality and Social Psychology, 70, 552-566. http://dx.

Muniz J., Garcia-Cueto E., & Lozano L. M. (2005). Item format and the psychometric properties of the Eysenck Personality Questionnaire. Personality and Individual Differences, 38, 61-69. paid.2004.03.021

O'Connor B. P. (2000). SPSS and SAS programs for determining the number of components using parallel analysis and Velicer's MAP test. Behavior Research Methods, Instrumentation, and Computers, 32, 396-402. http://dx.doi. org/10.3758/BF03200807

Ostendorf F., & Angleitner A. (1994). A comparison of different instruments proposed to measure the big-five. European Review of Applied Psychology, 44, 45-53.

Roberti J. W. (2004). A review of behavioral and biological correlates of sensation seeking. Journal of Research in Personality, 38, 256-279. S0092-6566(03)00067-9

Rolland J. P. (2002). The cross-cultural generalizability of the five-factor model of personality. In R. R. McCrae & J. Allik (Eds.). The five-factor model of personality across cultures (pp. 7-28). New York, NY: Kluwer Academic/Plenum Publishers.

Romero E., Luengo M. A., Gomez-Fraguela J. A., & Sobral J. (2002). La estructura de los rasgos de personalidad en adolescentes: El modelo de cinco factores y los cinco alternativos [The structure of personality traits on adolescents: The big-five and the alternative five models]. Psicothema, 14, 134-143.

Rosenblitt J. C., Soler H., Johnson S. E., & Quadagno D. M. (2001). Sensation seeking and hormones in men and women: Exploring the link. Hormones and Behavior, 40, 396-402.

Rossier J., Hansenne M., Baudin N., & Morizot J. (2012). Zuckerman's revised alternative Five-Factor Model: Validation of the Zuckerman-Kuhlman-Aluja Personality Questionnaire in Four French Speaking Countries. Journal of Personality Assessment, 94, 358-365. 10.1080/00223891.2012.657024

Shiomi K., Kuhlman D. M., Zuckerman M., Joreiman J. A., Sato M., & Yata S. (1996). Examining the validity of a Japanese version of the Zuckerman-Kuhlman Personality Questionnaire (ZKPQ). Hyago University of Teacher Education Journal, 2, 1-13.

Steiger J. H. (1990). Structural model evaluation and modification. Multivariate Behavioral Research, 25, 173-180.

Terracciano A., Abdel-Khalek A. M., Adam N., Adamovova L., Ahn C. K., Ahn H. N., ... & McCrae R. R. (2005). National character does not reflect mean personality trait levels in 49 cultures. Science, 310, 96-100. 10.1126/science.1117199

Tucker L. R. (1951). A method for synthesis of factor analysis studies (Personnel Research Section Report No. 984). Washington, DC: Department of the Army.

Tucker L. R., & Lewis C. (1973). A reliability coefficient for maximum likelihood factor analyses. Psychometrika, 38, 1-10.

Van Hemert D. A., Van de Vijver F. J. R., Poortinga Y. H., & Georgas J. (2002). Structural and functional equivalence of the Eysenck Personality Questionnaire within and between countries. Personality and Individual Differences, 33, 1229-1249. S0191-8869(02)00007-7

Wu Y.-X., Wang W., Du W.-Y., Li J., Jiang X.-F., & Wang Y.-H. (2000). Development of a Chinese version of the Zuckerman-Kuhlman personality questionnaire: Reliabilities and gender/age effects. Social Behavior and Personality, 28, 241-250. sbp.2000.28.3.241

Zuckerman M., Kuhlman D. M., Joireman J., Teta P., & Kraft M. (1993). A comparison of three structural models for personality: The big three, the big five, and the alternative five. Journal of Personality and Social Psychology, 65, 757-768.

Zuckerman M. (2002). Zuckerman-Kuhlman Personality Questionnaire (ZKPQ): An alternative five-factorial model. In B. de Raad & M. Perugini (Eds.), Big Five Assessment (pp. 377-396). Gottingen, Germany: Hogrefe & Huber.

Zuckerman M. (2005). Psychobiology of Personality, (2nd Ed.), revised and updated. New York, NY: Cambridge University Press.

Zuckerman M. (2008). Zuckerman-Kuhlman Personality Questionnaire (ZKPQ): An operational definition of the alternative Five factorial model of personality. In G. J. Boyle, G. Matthews, & D. H. Saklofske (Eds.), The SAGE handbook of personality theory and assessment: Vol. 2. Personality measurement and testing (pp. 219-238). Thousand Oaks, CA: Sage.

Zsuzsanna Suranyi [1] and Anton Aluja [2]

[1] University of the Reformed Church (Hungary)

[2] Universitat de Lleida (Spain)

Correspondence concerning this article should be addressed to Zsuzsanna Suranyi.1037 Becsi ut 324. Budapest (Hungary). Phone: +361M302348. Fax: +361-4302341.


This research was supported by the Spanish Ministerio de Ciencia e Innovacion (PSI2008-00924/PSIC). The study was performed within the framework of DURSI' Grup Consolidat 2009 SGR 809. Generalitat de Catalunya. Spain.

(1) [[eta].sup.2] < .0099 = negligeable; [[eta].sup.2] [greater than or equal to] .01: small; [[eta].sup.2] [greater than or equal to] .0588 medium; [[eta].sup.2] [greater than or equal to] .1379: large effect size (Cohen, 1988, pp. 274-288).

(2) [[eta].sup.2] < .0099 = negligeable; [[eta].sup.2] [greater than or equal to] .01: small; [[eta].sup.2] [greater than or equal to] .0588 medium; [[eta].sup.2] [greater than or equal to] .1379: large effect size (Cohen, 1988, pp. 274-288).

Table 1. Descriptives of samples

                            Catalan sample   Hungarian sample

Males                       466              1169
Age of males: mean (SD)     35.39 (12.16)    41.14 (13.24)
Females                     1098             465
Age of females: mean (SD)   31.33 (11.27)    38.93 (12.32)
Altogether                  1564             1647
Age: mean (SD)              32.57 (11.72)    39.88 (15.62)

Table 2. Descriptives, alpha internal consistencies,
and country differences

Catalan sample (n = 1,564)

b     M        SD      K       S       [alpha]

Age    32.54   11.68   -0.37    0.76   --
AG     85.24   16.32    0.03    0.28   92
AC    109.86   14.10   -0.11   -0.03   88
EX    119.22   16.67    0.17   -0.43   93
NE     94.10   19.56   -0.15    0.18   94
SS     89.28   16.63   -0.36    0.07   90
AG1    16.59    5.35    1.16    1.11   86
AG2    25.26    4.84   -0.18   -0.07   77
AG3    21.93    5.67   -0.27    0.27   87
AG4    21.47    4.49   -0.35   -0.02   71
AC1    25.01    5.39   -0.34    0.08   81
AC2    26.73    5.69   -0.44    0.03   86
AC3    27.61    4.36   -0.23   -0.03   67
AC4    30.51    4.31    0.06   -0.47   75
EX1    33.79    4.48    1.29   -0.94   83
EX2    30.86    6.01   -0.32   -0.44   90
EX3    25.48    5.48   -0.23    0.05   84
EX4    29.09    5.26   -0.08   -0.44   82
NE1    23.90    5.25   -0.02    0.05   80
NE2    23.18    5.69   -0.38    0.22   81
NE3    24.51    5.06   -0.09   -0.02   78
NE4    22.49    6.59   -0.45    0.26   91
SS1    21.79    6.36   -0.65    0.23   82
SS2    26.12    5.45   -0.33   -0.20   80
SS3    22.14    5.42   -0.45    0.10   81
SS4    19.22    3.68    0.12    0.17   65

Hungarian sample (n = 1,647)

M        SD      K       S       [alpha]   d

39.95    13.50   -0.45    0.86   --        -60
82.76    14.50    0.11    0.18   90         16
111.45   12.13    0.13    0.02   86        -12
118.43   13.85   -0.19   -0.01   91         05
78.83    15.61   -0.27    0.19   92         87
87.31    13.17    0.23   -0.08   86         13
19.94     5.19   -0.09    0.54   82        -63
24.64     3.94    0.70   -0.15   68         14
19.47     4.81    0.08    0.39   81         47
18.71     4.05   -0.31    0.09   72         64
24.45     4.24    0.40    0.04   67         13
28.62     4.72   -0.17    0.03   79        -40
24.59     3.30    0.76    0.34   50         78
33.79     4.52   -0.31   -0.58   86        -74
32.66     3.82    0.24   -0.41   76         27
30.91     4.25   -0.25   -0.14   79         00
26.08     4.52    0.06   -0.01   79        -12
28.78     4.48    0.27   -0.34   .78       0.06
18.34     4.61   -0.44    0.20   81        1.13
19.43     4.47   -0.25    0.21   75         73
21.86     3.93    0.07   -0.05   69         59
19.21     4.97   -0.20    0.32   84         57
22.57     5.33   -0.27   -0.02   76        -13
24.23     3.98    0.35   -0.05   61         40
21.59     4.35    0.15    0.15   72         12
18.91     3.71    1.21    0.50   71         08

M: Mean; SD: Standard deviation: K: Kurtosis; S: Skewness;
AG: Aggressiveness; AC: Activity; EX: Extraversion; NE:
Neuroticism; SS: Impulsive-Sensation Seeking; AG1: Physical
Aggression; AG2: Verbal Aggression; AG3: Anger; AG4:
Hostility; AC1: Work Compulsion; AC2: General Activity;
AC3: Restlessness; AC4: Work Energy; EX1: Positive Emotions;
EX2: Social Warmth; EX3: Exhibitionism; EX4: Sociability;
NE1: Anxiety; NE2: Depression; NE3: Dependency; NE4: Low
Self-Esteem; SS1: Thrill and Adventure Seeking); SS2:
Experience Seeking; SS3: Disinhibition; SS4: Boredom

Table 3. Factorial structure of the ZKA-PQ
and factorial congruency coefficients

                           Catalan Sample (n = 1,564)

                           I        II       III     IV       V

AG1: Physical Aggression    0.55#   -0.03    -0.13   -0.01     0.19
AG2: Verbal Aggression      0.76#   -0.03     0.14    0.03     0.19
AG3: Anger                  0.82#    0.05    -0.01    0.32     0.02
AG4: Hostility              0.66#   -0.04    -0.23    0.47#    0.11
AC1: Work Compulsion       -0.07     0.57#    0.02    0.06    -0.14
AC2: General Activity      -0.04     0.68#    0.07   -0.03     0.24
AC3: Restlessness           0.30     0.58#    0.13    0.09     0.19
AC4: Work Energy           -0.15     0.55#    0.23   -0.31    -0.28
EX1: Positive Emotions     -0.17     0.24     0.58#  -0.50#    0.05
EX2: Social Warmth         -0.14     0.10     0.76#  -0.15    -0.08
EX3: Exhibitionism          0.24     0.10     0.56#  -0.11     0.17
EX4: Sociability           -0.09     0.06     0.76#  -0.12     0.22
NE1: Anxiety                0.30     0.21    -0.11    0.73#    0.06
NE2: Depression             0.16    -0.05    -0.23    0.83#    0.05
NE3: Dependency             0.05     0.02     0.03    0.77#   -0.10
NE4: Low Self-Esteem       -0.02    -0.09    -0.25    0.86#    0.04
SS1: Thrill and             0.07     0.08    -0.05   -0.10     0.68#
  Adventure Seeking
SS2: Experience Seeking     0.04     0.01     0.10   -0.02     0.73#
SS3: Disinhibition          0.16     0.00     0.18    0.08     0.79#
SS4: Boredom                0.24    -0.03     0.06    0.09     0.56#
Eigenvalue                  5.03     3.84     2.15    1.64     1.57
% variance accounted       25.16    17.68    10.76    8.20     7.34

                           Hungarian sample
                           (n = 1,647)

                           I        II       III

AG1: Physical Aggression    0.65#   -0.06    -0.12
AG2: Verbal Aggression      0.75#   -0.02     0.05
AG3: Anger                  0.73#   -0.02    -0.09
AG4: Hostility              0.56#   -0.12    -0.33
AC1: Work Compulsion       -0.02     0.67#   -0.03
AC2: General Activity      -0.10     0.64#    0.16
AC3: Restlessness           0.27     0.39#    0.07
AC4: Work Energy           -0.14     0.69#    0.28
EX1: Positive Emotions     -0.17     0.31     0.57#
EX2: Social Warmth         -0.18     0.04     0.73#
EX3: Exhibitionism          0.14     0.10     0.60#
EX4: Sociability           -0.05     0.13     0.77#
NE1: Anxiety                0.19    -0.03    -0.27
NE2: Depression             0.16    -0.08    -0.32
NE3: Dependency             0.02    -0.02    -0.06
NE4: Low Self-Esteem        0.02    -0.08    -0.34
SS1: Thrill and             0.18     0.04     0.01
  Adventure Seeking
SS2: Experience Seeking     0.05     0.12     0.15
SS3: Disinhibition          0.21    -0.03     0.14
SS4: Boredom                0.20    -0.23    -0.12
C.C                         0.98     0.95     0.98
Eigenvalue                  1.93     1.18     3.42
% variance accounted        6.63     5.91    17.09
                           Hungarian sample
                           (n = 1,647)

                           IV       V           C.C.

AG1: Physical Aggression   -0.02     0.31       0.99
AG2: Verbal Aggression      0.02     0.17       0.99
AG3: Anger                  0.39     0.11       0.99
AG4: Hostility              0.53#    0.17       0.99
AC1: Work Compulsion        0.07     0.03       0.96
AC2: General Activity      -0.22     0.03       0.89
AC3: Restlessness           0.16     0.23       0.98
AC4: Work Energy           -0.33    -0.28       1
EX1: Positive Emotions     -0.46#   -0.09       0.98
EX2: Social Warmth         -0.30    -0.08       0.97
EX3: Exhibitionism         -0.24     0.30       0.95
EX4: Sociability           -0.22     0.21       0.96
NE1: Anxiety                0.78#    0.04       0.99
NE2: Depression             0.76#    0.01       1
NE3: Dependency             0.77#   -0.10       0.98
NE4: Low Self-Esteem        0.78#   -0.03       0.98
SS1: Thrill and            -0.13     0.67#      0.98
  Adventure Seeking
SS2: Experience Seeking    -0.06     0.62#      0.98
SS3: Disinhibition          0.07     0.76#      1
SS4: Boredom                0.20     0.50#      0.90
C.C                         0.98     0.97       0.97
Eigenvalue                  6.12     1.30
% variance accounted       30.59     6.52

Note: Values above 0.40 are shown in boldface.
CC: Congruence coefficients.

Note: Values above 0.40 are indicated with #.

Table 4. Goodness of fit indices for ZKA-PQ models

Oblique five-factor models      [chi square] *   df    [chi square]/df

Catalan (n = 1,564)
Simple structure                4533.112         160   28.33
Salient loadings (> 0.30)       2958.191         154   19.21
Modest loadings (> 0.15)        1708.87          137   12.47
[Correlated error terms.sup.    1338.180         134    9.99
Hungarian (n = 1,647)
Simple structure                4336.692         160
Salient loadings (>0.30)        3033.128         150   27.10
Modest loadings (>0.15)         1369.753         127   20.22
[Correlated error terms.sup.    1296.283         124   10.79

Oblique five-factor models      GFI    TLI    CFI    RMSEA

Catalan (n = 1,564)
Simple structure                0.76   0.67   0.72   0.132
Salient loadings (> 0.30)       0.84   0.78   0.72   0.108
Modest loadings (> 0.15)        0.90   0.86   0.90   0.086
[Correlated error terms.sup.    0.92   0.89   0.92   0.076
Hungarian (n = 1,647)
Simple structure                0.77   0.71   0.76   0.126
Salient loadings (>0.30)        0.77   0.80   0.83   0.108
Modest loadings (>0.15)         0.92   0.89   0.93   0.077
[Correlated error terms.sup.    0.92   0.90   0.93   0.076

Oblique five-factor models      (90% CI)

Catalan (n = 1,564)
Simple structure                (0.129-0.136)
Salient loadings (> 0.30)       (0.105-0.111)
Modest loadings (> 0.15)        (0.082-0.089)
[Correlated error terms.sup.    (0.072-0-082)
Hungarian (n = 1,647)
Simple structure                (0.123-0.129)
Salient loadings (>0.30)        (0.105-0.111)
Modest loadings (>0.15)         (0.073-0.081)
[Correlated error terms.sup.    (0.072-0.080)

Note: * The associated p values were always lower than 0.001;
d.f. Degree of freedom; GFI: Goodness of fit index; TLI:
Tucker-Lewis index; CFI: Comparative Fit Index; RMSEA: root
mean square error of approximation and its 90% confidence
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Title Annotation:articulo en ingles
Author:Suranyi, Zsuzsanna; Aluja, Anton
Publication:Spanish Journal of Psychology
Date:Jan 1, 2014
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