Self-reported psychopathic traits among non-referred Finnish adolescents: psychometric properties of the Youth Psychopathic traits Inventory and the Antisocial Process Screening Device
© Oshukova et al. 2015
Received: 9 February 2015
Accepted: 28 May 2015
Published: 6 June 2015
In general psychiatric services, cost-benefit screening instruments for psychopathic traits in adolescents are needed. The aim of the present study was to study the psychometric properties of the Finnish versions of the Youth Psychopathic traits Inventory (YPI) and the Antisocial Process Screening Device (APSD-SR) in community youth. As gender-specific differences exist in psychopathic traits, we analyzed the data separately in girls and boys.
The YPI and the APSD-SR were administered to 372 9th graders (174 boys and 198 girls) with a mean age of 15.06 years (SD 0.28). Cronbach’s alphas were used to study internal consistency. The factor structures of the self-assessments were studied using both Confirmatory Factor Analysis (CFA) and Principal Component Analysis (PCA).
In both self-assessments, boys scored significantly higher in the total scores, Interpersonal and Affective dimension scores as well as in most sub-dimensions. In the YPI, the alpha values for total and dimensional scores ranged from 0.55 to 0.91 in boys and from 0.74 to 0.89 in girls and, in the APSD-SR, respectively, from 0.38 to 0.78 and from 0.29 to 0.78. In CFA, the three-factor model produced poor fit for both self-assessments. For the ten sub-dimensions of the YPI, the PCA suggested two factors. Extending the model into three components showed sub-dimension loadings according to the original dimensions. For the APSD-SR, the PCA revealed a five-factor structure in the male sample and a six-factor one in the female group. When limiting the model to a three factor- model, we obtained a structure, which resembled the original dimensions.
Both the YPI and the APSD-SR are promising tools of screening for psychopathic features in Finnish community youth. The YPI turned out to be slightly better than the APSD- SR in both reliability and factor structure. However, the original three-factor models did not find support. Both self-assessments were somewhat weak for tapping the callous-unemotional traits of the psychopathic character, but, again, the YPI worked better than the ASPD-SR. Both self-assessments revealed significant gender differences in psychopathic character traits.
KeywordsPsychopathic traits Adolescence The Youth Psychopathic traits Inventory The Antisocial Process Screening Device Psychometric properties
A personality trait is a more or less stable way of experiencing and perceiving oneself and one’s surroundings, as well as relating to others. Deficient interpersonal (superficial charm, grandiose sense of self-worth and manipulation), affective (shallow affect, lack of empathy, lack of remorse or guilt), and behavioral (impulsivity, failure to carry responsibility for one’s own actions) characteristics comprise psychopathic character traits. According to the current conception, psychopathic traits are a continuum of features that each individual exhibits to a certain extent, and psychopathy is a malicious conceptualization of the extremes of normal personality traits [1, 2].
Psychopathic traits are described as relatively stable over time from childhood through adolescence to adulthood . Adolescents with psychopathic traits are stimulus seeking , more reactive to reward than punishment  and more likely to violate social norms of society and engage in antisocial behavior [6–8]. Besides more severe aggression, youth with elevated psychopathic traits display more instrumental and premeditated aggression compared to other adolescents with severe conduct problems . Furthermore, psychopathic traits are associated with an earlier onset to severe conduct problems . Psychopathic traits in adolescents are strongly related to various mental disorders  and drug use . Poor treatment compliance and a high drop-out rate in mental health services have also been linked to high traits of psychopathy . However, recent research has suggested that adolescents with elevated psychopathic traits are not “untreatable” and that they can improve with intensive interventions tailored to their unique emotional, cognitive, and motivational styles . The real challenge for the mental health services is that they should be able to detect these adolescents.
Research on the relative prevalence rates of psychopathic traits in boys and girls is mixed, with some studies reporting overall higher psychopathic tendencies among boys than among girls, and others finding no gender differences . It has been stated, that higher psychopathy scores for boys than for girls tend to emerge in samples recruited from community settings, while studies among justice-involved youth have reported fewer differences in psychopathic scores across the genders . All in all, more research is needed on gender differences in psychopathic character traits in adolescence.
The gold standard for assessing adolescent psychopathic traits is the Psychopathy Checklist- Revised: Youth version . This is, however, a time-consuming method that demands rigorous training and is mainly used in forensic samples. General psychiatric services have a need for cost-beneficial screening instruments for adolescent populations. This need became even more urgent in 2013, as a subtype of conduct disorder characterized by callous-unemotional traits was introduced in the fifth version of the Diagnostic and Statistical Manual of Mental Disorders (DSM 5) . Both the Youth Psychopathic traits Inventory (YPI)  and the Antisocial Process Screening Device - Self Report (APSD-SR)  are questionnaires designed to assess psychopathic traits among 13- to 18-year-old community youth. Both of these self-assessments measure the interpersonal, affective and behavioral dimensions of psychopathy and have shown acceptable psychometric properties [11, 18–20]. There are, however, some differences between these two self-questionnaires. The APSD-SR contains one item for each of the 20 items measured by the Hare Psychopathy Checklist - Revised , the precursor of self-assessments measuring psychopathy, whereas the YPI assesses each psychopathic trait with several items. The APSD-SR tends to ask about psychopathy-like behavior directly (e.g. “I lie easily and skillfully”, “I blame others for my mistakes”), but in the YPI, the items are composed to tap psychopathic traits more indirectly, framing the psychopathic features as abilities, rather than deficits (e.g. “I usually feel calm when other people are scared” instead of “My emotions are shallow”) .
The current language versions of the self-assessments are extremely important to study before extensive use since the translation might not capture the meaning of the item adequately and cultural characteristics affect the comprehensiveness of the items. The aim of the present study was to study the psychometric properties of the Finnish versions of the YPI and the APSD-SR in Finnish community youth. As gender-specific differences have been reported in studies performed with these instruments [4, 11, 20, 22] we analyzed the data separately in girls and boys. We hypothesized that, in line with previous studies among justice-involved youth [23, 24], the YPI would appear to be slightly better in tapping psychopathic traits than the APSD-SR. Our second hypothesis was that both self-assessments would reveal significant gender differences.
The sample comprised 15- to 16-year-old Finnish-speaking adolescents attending the 9th grade at secondary schools in the city of Kokkola, on the western coast of Finland, in January 2014. Kokkola is the 23rd largest town in Finland with approximately 47 000 citizens. Eighty-four percent of its citizens speak Finnish, 13 % Swedish and 3 % some other language as their mother tongue.
Of the 446 students in five secondary schools, 60 (13.4 %) did not participate in the study because of either not attending school on the study day or refusing participation. Of the remaining 386 students, eight did not complete the self-assessments and six did not provide the collected background variables asked for in the questionnaire, and thus were excluded from the analysis. The final sample comprised 372 adolescents with a mean age of 15.06 years (SD 0.28), of whom 174 (46.8 %) were boys and 198 (53.2 %) girls.
The YPI  consists of 50 statements scored on a 4-point Likert scale with response options ranging from “Does not apply at all = 1” to “Applies very well = 4”; thus, the total score of the scale can range from 50 to 200, with a higher score representing a higher level of the trait. The YPI has three dimensions (factors) and 10 sub-dimensions. The Interpersonal (Grandiose-manipulative) dimension consists of sub-dimensions named Dishonest charm, Grandiosity, Lying and Manipulation, the Affective (Callous-unemotional) dimension of Remorselessness, Unemotionality and Callousness, and the Behavioral (Impulsive-irresponsible) dimension of Thrill-seeking, Impulsiveness and Irresponsibility. All sub-dimensions are scored with five items. In this study we used the authorized Finnish translation of the YPI, which was commissioned by the authors. An iterative process of translation and independent back translation was used, followed by a discussion to resolve minor differences.
The APSD  was originally developed to study children aged 6 to 13 years, but, later, it has been used as a self-assessment (APSD-SR) tool for adolescent populations [23–25]. It consists of 20 statements scored on a 3-point scale (0 = not at all true, 1 = sometimes true, 2 = definitely true), the total score of the scale ranging from 0 to 40, with a higher score representing a higher level of the trait. The three dimensions (factors) of the scale are Interpersonal (Narcissism), Affective (Callous/unemotional) and Behavioral (Impulsivity). In the present study, the authorized Finnish translation of the APSD-SR was used .
The present study is a part of an on-going study project investigating psychopathic traits among Finnish adolescents. The adolescents completed the above mentioned self-assessments together with the Youth Self Report (YSR) during their regular school classes. Prior to completing the assessments, they received information about the study both orally and in a cover letter. The participants were assured of the confidentiality and anonymity of the data and of the voluntary nature of participation. Return of the completed questionnaires from the participants was taken as confirmation of their consent. Privacy was ensured by including no identifying factors in the questionnaires; only age and gender were collected as background variables. A letter was sent to the guardians of the students to inform them about the study, and they had the opportunity to familiarize themselves with the self-assessments. The adolescents and parents were informed that the study aimed to investigate adolescents’ thoughts, ideas and feelings towards different aspects of life as well as adolescents’ behavior and well-being. Further, the adolescents were informed that they had an opportunity to contact the researchers (e-mails and telephone numbers were offered) if the content of the self-assessments raised questions or ideas, which they wanted to share with the researchers. The study plan was evaluated by the Ethics Committee of the Helsinki and Uusimaa Hospital District. Permission to conduct the study was granted by the administration of the schools.
In order to evaluate the internal consistency of both the YPI and the APSD-SR, we calculated Cronbach’s alphas for the total and dimensional scores, as well as for the sub-dimensional scores of the YPI. In line with previous research, reliability coefficients of < 0.60 were interpreted as insufficient, 0.60 to 0.69 as marginal, 0.70 to 0.79 as acceptable, 0.80 to 0.89 as good, and 0.90 as excellent .
We provided descriptive information concerning the distribution of the YPI and the APSD-SR scores separately for boys and girls. Average continuous scores were reported. According to the skewness and kurtosis, some of the variables were not normally distributed. While looking closer on the distribution skewness, we found that it was mostly due to a small group of participants (three boys and two girls) with very high scores. We also checked the main statistical parameters with omission of these five adolescents, and the omission did not influence the results. So, we proceeded with the whole sample using non-parametric tests. The Mann–Whitney U-test was used to test the group differences. We also calculated Cohen’s d to estimate the effect sizes of the gender differences, interpreting an effect size of 0.2 to 0.5 as small, 0.5 to 0.8 as medium, and over 0.8 as large . The convergent validity of the YPI and the APSD-SR was explored by calculating Spearman’s correlations. As recommended , we considered a Spearman’s coefficient of 0.1 to 0.3 as small, 0.3 to 0.5 as moderate, and >0.5 as high.
We attempted to replicate the three-component structure of the self-assessments with the Confirmatory Factor Analysis (CFA), performed with the Mplus 7 statistical software . To check the fit of the model to our data, we used the Chi-square Test of model fit for the baseline model, the Comparative Fit Index (CFI), and the Root Square Error of Approximation (RMSEA). The CFI values > 0.90 indicated a reasonably good fit, and in RMSEA, values < 0.06 indicated an acceptable model fit. As the fits assessed using the CFA were not adequate, we performed a Principal Component Analysis (PCA) with oblique Promax rotation to explore the factor structure of the self-assessments. The oblique rotation method was used in line with the previous research , as we wanted to let the factors correlate with each other.
For both self-assessments, we checked the number of factors using the Kaiser criterion (i.e. eigenvalues >1) and a scree plot. The three-factor structure was analyzed for both assessments for comparability with the previous studies [11, 20, 25, 29]. According to Kline , loadings of 0.30 or higher were considered significant. All the statistical analyses except the CFA were performed with IBM SPSS Statistics version 19.
Descriptives and mean group differences in the Youth Psychopathic traits Inventory (YPI) and the Antisocial Process Screening Device-self-report (APSD-SR) scores between 15- to 16-year-old boys (n = 174) and girls (n = 198) attending the 9th grade at 5 secondary schools in Finland. Comparisons are performed using the Mann–Whitney U-test. Effect sizes (Cohen’s d) are reported
Skewness (SE = 0.184)
Kurtosis (SE = 0.366)
Skewness (SE = 0.173)
Kurtosis (SE = 0.344)
Mann–Whitney U Test
Internal consistencies for the sub-dimensions, dimensions and the total score of the Youth Psychopathic traits Inventory (YPI) and the dimensions and total score of the Antisocial Process Screening Device - self-report (APSD-SR) in 15- to 16-year-old boys (n = 174) and girls (n = 198) attending the 9th grade in 5 secondary schools in Finland
YPI Dishonest charm
YPI Interpersonal dimension
YPI Affective dimension
YPI Behavioral dimension
YPI Total score
APSD-SR Interpersonal dimension
APSD-SR Affective dimension
APSD-SR Behavioral dimension
APSD-SR Total score
For the APSD-SR, Cronbach’s alphas showed acceptable internal consistencies for the total score in both genders. As for the dimensional scores, the internal consistency was acceptable for the Interpersonal, marginal for the Behavioral and insufficient for the Affective dimension in both genders.
Spearman’s correlations between the dimensional and total scores of the Youth Psychopathic traits Inventory (YPI) and the Antisocial Process Screening Device -self report (APSD-SR) in 15-to 16-year-old boys (n = 174) and girls (n = 198) attending the 9th grade in 5 secondary schools in Finland
In Table 3, the correlations between the YPI and the APSD-SR are presented. In both genders, the total scores as well as the Interpersonal and Behavioral dimension scores of the YPI and the APSD-SR were highly correlated with each other, but the correlation between the Affective dimension scores of the two instruments was only weak.
The CFA, which was performed for the 10 sub-dimensions of the YPI, did not support the hypothesized factor solution in boys and did not converge in girls. We attempted to replicate the three-factor model on the item level. For both self-assessments, the three-factor model produced a poor fit (YPI: boys/girls: x 2 = 2461/4924, df = 1172/1225, CFI = 0.680/0.670, RMSEA = 0.080/0.072; APSD-SR: boys/girls: x 2 = 610/512, df = 169/169, CFI = 0.475/0.546, RMSEA = 0.123/0.101). The items loaded mostly in a theoretically meaningful way, with the exception of some YPI items constituting the Callousness sub-scale (boys: items 23, 35 and 49; girls: items 35 and 49) and, respectively, some APSD-SR Items constituting the Affective dimension (boys: items 3, 7, 12, 18, and 20; girls: items 3 and 19). In these cases, loading indices were insufficient. For details, see the Additional file 1.
Loading of the sub-dimensions of the Youth Psychopathic traits Inventory (YPI) and items of the Antisocial Process Screening Device -self report (APSD-SR) into three factors in boys (n = 174) and girls (n = 198)
YPI Sub-dimension/APSD-SR Item
5 Shallow emotions
8 Brags about accomplishments
10 Uses or cons others
11 Teases other people
14 Charming in insincere ways
15 Becomes angry when corrected
16 Thinks he is more important
1 Blames others for mistakes
9 Gets bored easily
4 Acts without thinking
13 Engages in risky and dangerous behavior
17 Does not plan ahead
19 Does not show emotions
7 Keeps promises (Reversely = R)
12 Feels bad or guilty
18 Concerned about the feelings of others (R)
20 Keeps the same friends (R)
3 Concerned about schoolwork(R)
6 Lies easily and skillfully
2 Engages in illegal activities
For the APSD-SR, the PCA revealed a five-factor structure in boys and a six-factor one in girls, with eigenvalues greater than one, accounting for 59 and 60 % of the total variance, respectively. When limiting the model to three-factor model, we obtained a structure which resembled the original dimensions. However, in both genders, item six (Lies easily and skillfully) loaded on two factors (interpersonal and behavioral). Further, item one (Blames others for mistakes) loaded on the interpersonal factor in boys, but on the behavioral one in girls, item five (Shallow emotion) on the behavioral factor in boys, but on the interpersonal one in girls, item 15 (Becomes angry when corrected) on the interpersonal factor in girls, but on both interpersonal and affective ones in boys, and item 19 (Does not show emotions) on the interpersonal factor in boys, but on the behavioral one in girls. Item three (Concerned about schoolwork, coded reversely) loaded negatively on the behavioral factor in both genders.
This study was to first to study the psychometric properties of the Finnish versions of the YPI and the APSD-SR in the same adolescent community sample. Previous research has revealed that the YPI is internally consistent among non-referred boys and girls [11, 20]. Our study largely supported these previous results, since we found good or even excellent internal consistencies of the YPI total as well as Interpersonal and Behavioral dimension scores in both genders. However, in line with some previous studies performed both in community and forensic samples [20, 31, 32], the internal consistency of the Affective dimension was only acceptable in girls and even insufficient in boys. Correlations between the total and dimensional scores proved to be strong.
In a recent community study using the APSD-SR by Pechorro et al.  among 510 mid-adolescent Portuguese pupils, the internal consistency was acceptable for the total score, marginal for the interpersonal dimension, but insufficient for the affective and behavioral dimensions. Accordingly, in our study, Cronbach’s alpha showed acceptable internal consistency for the total score and insufficient internal consistency for the Affective dimension in both genders. However, in the present study, the internal consistency was acceptable for the Interpersonal and marginal for the Behavioral dimensions. A recent Finnish community study among 4855 9th graders by Laajasalo et al.  reported internal consistency indices for the APSD-SR total as well as for the Interpersonal and Behavioral dimension scores, which were highly consistent with our results (α: 0.70–0.76). However, in their study, the Affective dimension exhibited better reliability (α = 0.67) than was seen in our work. Focusing on correlations, both in our study and in the study by Laajasalo et al., the Affective dimension score correlated only modestly with the two other dimensional scores.
Comparison between the YPI and the APSD-SR
As far as the authors are aware, only two previous studies have compared the psychometric properties of the YPI and the APSD-SR in adolescents [23, 24]. Both studies were performed among delinquents and reported that both self-assessments were somewhat weak for tapping the affective traits of psychopathy; however, the YPI appeared to be slightly better than the APSD-SR. Our results with mid-adolescent community youth support this finding. It has been argued that the reason for this might be the substantial differences between the scales: the YPI comprises more items and taps psychopathic traits more indirectly than the APSD-SR [23, 24]. Interestingly, in the present study, and in line with that of Colins et al. , the YPI Interpersonal dimension was strongly related to the Affective dimension, as well as to the Behavioral one. What comes to APSD-SR dimensions, only the latter correlation was significant. Thus, the question rises whether the APSD-SR rather taps antisocial behavior features than the other elements of psychopathic character traits. This idea is not new, as the need for further revision has been stated concerning the APSD-SR . The developers of the YPI have also proposed that the current number of items, even though higher than in the APSD-SR, is not high enough to detect the sub-dimensions comprising the Affective dimension and, because of this, the instrument may need further revision . In addition, the development of new instruments is an important area of the future work. One unpleasant thought is, however, that the affective dimension of psychopathic character traits may simply be too difficult to self-evaluate among adolescents. If this is the case, the self-assessment should always be strengthened by a clinical interview. All in all, the screening instrument’s ability to assess the affective dimension is extremely important since, according to many researchers, it is the affective and interpersonal features that comprise the “core” of the psychopathy [11, 34], foreshadowing a great risk of long-term maladjustment in children and adolescents [35, 36].
Some researchers have reported higher psychopathic tendencies among adolescent boys than among girls, both in community and forensic samples, and others have found no gender differences or differences in certain traits. These inconsistent findings may be dependent upon the developmental period of the studied adolescents, the study method, the sample selection and the particular dimension of psychopathy being assessed . In line with a recent community study performed using the YPI among Dutch 9th graders , our study revealed significantly higher total as well as Interpersonal and Affective dimension scores in boys than in girls. However, the Dutch study reported that boys scored significantly higher also in the Behavioral dimension, which we were not able to find. According to a recent study by Asgeirsdottir and Sigfusdottir , girls in Nordic countries tend to report higher levels of anger symptoms than boys. Whether the observed lack of gender difference in antisocial behavior reflects social, educational and economic gender equality characteristics of all Nordic countries, comprises an interesting question to be studied in the future. In our sample, no gender difference was observed on Manipulation and Dishonest charm, both reflecting the Interpersonal dimension of the YPI. Among the Dutch sample, boys scored significantly higher on these items also . These findings are interesting, since deliberate manipulation of peer relationships by, for example, ostracism, gossiping and telling lies about the victims has been seen as a typical female phenomenon, and among adults, the prototypical psychopathic woman exhibits more manipulation than the prototypical psychopathic man does . All in all, cultural aspects seem to have an impact on gender differences in psychopathic character traits already in adolescence.
In our study, the same gender differences emerged in the APSD-SR total as well as in the dimensional scores observed in the YPI, which speaks for the validity of the two measures. We were not able to find studies focusing on gender differences in APSD-SR scores in mid-adolescent community youth, but in a study performed using the teacher and parent versions of the APSD among children with a mean age of 10.7 years, boys scored higher on all three dimensions . The authors reported that the difference was stronger in older grade cohorts. However, Vitacco et al.  found no gender differences in a sample of delinquent youth. Again, Poythress et al.  were not able to find any gender differences on either the APSD-SR or the YPI in a sample of justice-involved adolescents with a mean age of 14.4 years. Overall, findings on gender differences have been inconsistent depending upon the developmental stage of the studied individuals, the study method, the sample selection, and the particular dimension of psychopathy being assessed . Studies among adult samples have, however, repeatedly revealed that significant differences between genders exist .
Factor analysis of the YPI and the APSD-SR
When studying the psychometric properties of the inventories, the factor structure analysis is of great importance, since replication of the factor structure in different samples increases confidence in the usefulness of the composite scores . We chose the three-factor model for the CFA, because the current literature on the factor structure mostly discusses three or four factors underlying the psychopathy construct [33, 41, 42], and the three-component structure of both the YPI and the APSD-SR has been demonstrated [11, 17, 20, 25]. For both self-assessments, and in both genders, the three-factor model produced a poor fit. However, the fit indices for the YPI proved to be slightly better than those for the APSD-SR. Further, for both measures, the fit was slightly better in girls than in boys. One explanation of our, to some extent unexpected, results with the poor fit might be the relatively small sample size. Though the YPI three-factor structure has received confirmation in numerous studies using the CFA [11, 22, 24], in a study by Poythress et al.  in a sample of justice-involved adolescents, the CFA results indicated only a marginal fit of the three-factor model for the data.
In the YPI, the PCA suggested a structure of two factors with eigenvalues greater than one. This was not, however, theoretically interpretable in boys, among whom all sub-dimensions except Callousness loaded on the same factor. The three-component model, even though statistically weaker, showed sub-dimension loadings similar to that recommended by the developers of the YPI , although in boys, the sub-dimensions Unemotionality and Remorselessness loaded on the interpersonal factor instead of the affective one. In girls, these two sub-dimensions loaded on both the interpersonal and affective factors, which has been reported previously [11, 20]. In a study by Hillege et al. , in boys, Lying loaded on both interpersonal and behavioral factors, but this was not observed in the present sample.
On the APSD-SR, the PCA revealed a five-factor structure in boys and a six-factor in girls. When the model was forced into three factors, we received a loading structure, which resembled that reported in the original study . In a Finnish community study , the three-factor model produced a close to an adequate fit, and the exploratory factor analysis confirmed three conceptually meaningful factors, resembling previously found ones. In our study, unlike in studies by Frick et al.  and Vitacco et al. , item three, reversely coded “Concerned about schoolwork”, did not load on the affective factor as expected, but instead negatively on the behavioral factor. Interestingly, this same finding was observed by Laajasalo et al. . The authors suggested as one possible explanation that the Finnish school system is less test-driven compared with many other countries. Item nineteen, “Does not show emotions”, loaded on the interpersonal factor in boys, but on the behavioral one in girls. According to earlier research, this item has exhibited poor performance characteristics as well as low factor loadings [25, 39], and it has even been excluded from the three-factor model due to poor fit . All in all, multiple inconsistent loadings of the APSD-SR items, observed also in the present study, have raised concern since interpretation of the dimensional scores is difficult if the items, which comprise the dimension do not neatly cluster into it [23, 24, 39]. It is difficult to interpret to what extent our findings reflect actual problems in loading and to what extent gender differences. We were not able to find studies focusing on gender differences in the APSD-SR factor structure in mid-adolescent community youth, but in the work of Frick et al. , among children with a mean age of 10.7 years, less clear differentiation between the interpersonal and behavioral items was observed in girls than in boys, with many items showing double loadings. Obviously, more research is needed to compare the factor structure of both self-assessments between the genders.
Obviously, more research is needed to explore the factor structure of both self-assessments in larger samples, across gender and culture.
Strengths and limitations
An obvious strength of the present study is the good participation rate and the sample distribution, with an almost equal number of girls and boys. However, all respondents were 15–16 years old, and the findings cannot be generalized to other age groups. Further, the adolescents were not clinically interviewed, and the ratings were based on self-reports. Moreover, the sample size was relatively small, which might explain the poor results of the factor analyses. The variance distribution for some items showed asymmetry. To avoid result bias caused by distribution skewness, we used non-parametric tests. Future studies in adolescent samples with different age ranges, cultures and ethnicity are obviously needed. The present study can be seen as a preliminary validation study and future studies among Finnish adolescent psychiatric patients should be performed before the self-questionnaires are put into use in adolescent psychiatric services.
Both the YPI and the APSD-SR are promising tools to screen for psychopathic features in Finnish community youth. Among non-referred mid-adolescents, the YPI was slightly better than the APSD- SR in both reliability and factor structure, though the original three-factor models did not gain support. Unfortunately, both self-assessments were somewhat weak for tapping the callous-unemotional traits of the psychopathic character; however, the YPI worked better than the ASPD-SR. Both self-assessments revealed significant gender differences in psychopathic character traits.
- Widiger TA, Lynam DR. Psychopathy and the five factor model of personality. In: Millon T, Simonsen E, Briket-Smith M, Davis RD, editors. Psychopathy: Antisocial, criminal, and violent behavior. New York: The Guilford Press; 1998.Google Scholar
- Benning SD, Patrick CJ, Blonigen DM, Hicks BM, Iacono WG. Estimating facets of psychopathy from normal personality traits: a step toward community epidemiological investigations. Assessment. 2005;12:3–18.PubMed CentralPubMedView ArticleGoogle Scholar
- Frick PJ, Ray JV, Thornton LC, Kahn RE. Can callous-unemotional traits enchance the understanding, diagnosis, and the treatment of serious conduct problems in children and adolescents? A comprehensive review. Psychol Bull. 2014;40:1.57.Google Scholar
- Frick PJ, O’Brien BS, Wootton JM, Mc Burnett K. Psychopathy and conduct problems in children. J Abnorm Psychol. 1994;103:700–7.PubMedView ArticleGoogle Scholar
- O’Brien BS, Frick PJ. Reward dominance: associations with anxiety, conduct problems, and psychopathy in children. J Abnorm Psychol. 1996;24:223–40.View ArticleGoogle Scholar
- Kimonis ER, Frick PJ, Barry CT. Callous-unemotional tarits and delinquent peer affiliation. J Consult Clin Psychol. 2004;7:956–66.View ArticleGoogle Scholar
- Dadds MR, Fraser J, Frost A, Hawes DJ. Disentangling the underlying dimensions of psychopathy and conduct problems in childhood: a community study. J Consult Clin Psychol. 2005;73:400–10.PubMedView ArticleGoogle Scholar
- Lynam DR, Miller DJ, Vachon D, Loeber R, Stouthamer-Loeber M. Psychopathy in adolescence predicts official reports of offending in adulthood. Youth Violence Juv Justice. 2009;7:189–207.PubMed CentralPubMedView ArticleGoogle Scholar
- Dandreaux DM, Frick PJ. Developmental pathways to conduct problems: a further test of the childhood and adolescent-onset distinction. J Abnorm Child Psychol. 2009;37:375–85.PubMedView ArticleGoogle Scholar
- Forth AE, Burke HC. Psychopathy in adolescence: assessment, violence and developmental precursors. In: Cooke DJ, Forth AE, Hare RD, editors. Psychopathy: Theory, research and implications for society. Boston: Kluwer; 1998.Google Scholar
- Andershed H, Gustafson SB, Kerr M, Stattin H. The usefulness of self-reported psychopathy-like traits in the study of antisocial behavior among non-referred adolescents. Eur J Pers. 2002;16:383–402.View ArticleGoogle Scholar
- O’Neill ML, Lidz V, Heilbrun K. Adolescents with psychopathic characteristics in a substance abusing cohort: treatment process and outcomes. Law Hum Behav. 2003;27:299–313.PubMedView ArticleGoogle Scholar
- Frick PJ, Ray JV, Thornton LC, Kahn RE. A developmental psychopathology approach to understanding callous-unemotional traits in children and adolescents with serious conduct problems. J Child Psychol Psychiatr. 2014;55:532–48.View ArticleGoogle Scholar
- Verona E, Sadeh N, Javdani S. The influence of gender and culture on child and adolescent psychopathy. In: Salekin R, Lynam D, editors. Handbook of child & adolescent psychopathy. New York: The Guilford Press; 2010.Google Scholar
- Forth AE, Kosson DS, Hare RD. The Hare PCL: YV. Toronto: Multi-Health Systems; 2003.Google Scholar
- American Psychiatric Association. Diagnostic and statistical manual of mental disorders. 5th ed. Washington DC: American Psychiatric Press; 2013.Google Scholar
- Frick PJ, Hare RD. The antisocial screening device. Toronto: Multi-Health Systems; 2001.Google Scholar
- Falkenbach D, Poythress NG, Heide KM. Psychopathic features in a juvenile diverse population: Reliability and validity of two self-report measures. Behav Sci Law. 2003;21:787–805.PubMedView ArticleGoogle Scholar
- Spain SE, Douglas KS, Poythress NG, Epstein M. The relationship between psychopathic features, violence, and treatment outcome: The comparison of three youth measures of psychopathic features. Behav Sci Law. 2004;22:85–102.PubMedView ArticleGoogle Scholar
- Hillege S, Das J, de Ruiter C. The Youth Psychopathic traits Inventory: psychometric properties and its relation to substance use and interpersonal style in a Dutch sample of non-referred adolescents. J Adolesc. 2010;33:83–91.PubMedView ArticleGoogle Scholar
- Hare RD. The hare psychopathy checklist—Revised. Toronto: Multi-Health Systems; 1991.Google Scholar
- Larsson H, Andershed H, Lichtenstein P. A genetic factor explains most of the variation in the psychopathic personality. J Abnorm Psychol. 2006;115:221–30.PubMedView ArticleGoogle Scholar
- Poythress NG, Dembo R, Wareham J, Greenbaum PE. Construct validity of the Youth Psychopathic traits Inventory (YPI) and the Antisocial Process Screening Device (APSD) with justice involved adolescents. Crim Justice Behav. 2006;33:26–55.View ArticleGoogle Scholar
- Colins OF, Bijttebier P, Broekaert E, Andershed H. Psychopathic-like traits among detained female adolescents: reliability and validity of the Antisocial Process Screening Device and the Youth Psychopathic traits Inventory. Assessment. 2014;2:195–209.View ArticleGoogle Scholar
- Laajasalo T, Saukkonen S, Kivivuori J, Salmi V, Lipsanen J, Aronen E. Brief report: Self-reported psychopathic-like features among Finnish community youth: Investigation of the factor structure of the antisocial personality screening device. J Adolesc. 2014;37:1185–8.PubMedView ArticleGoogle Scholar
- Barker C, Pistran N, Elliot R. Research methods in clinical and counseling psychology. Chichester, England: Wiley; 1994.Google Scholar
- Cohen J. A power primer. Psychol Bull. 1992;112:155–9.PubMedView ArticleGoogle Scholar
- Muthen LK, Muthen BO. Mplus User’s guide. 7th ed. Los Angeles, CA: Muthen & Muthen; 2012.Google Scholar
- Frick PJ, Bodin SD, Barry CT. Psychopathic traits and conduct problems in community and clinic-referred samples of children: further development of the psychopathy screening device. Psychol Assess. 2000;12:382–93.PubMedView ArticleGoogle Scholar
- Kline P. An easy guide to factor analysis. London: Routledge; 2002.Google Scholar
- Skeem JL, Cauffman E. Views of the downward extension: comparing the youth version of the psychopathy checklist with the youth psychopathic traits inventory. Behav Sci Law. 2003;21:737–70.PubMedView ArticleGoogle Scholar
- Andershed H, Hodgins S, Tengström A. Convergent validity of the Youth psychopathic traits Inventory (YPI): association with the Psychopathy Checklist: Youth Version (PCL-YV). Assessment. 2007;14:144–54.PubMedView ArticleGoogle Scholar
- Pechorro P, Maroco J, Poiares C, Vieira RX. Validation of the Portuguese version of the antisocial process screening device-self-report with a focus on delinquent behavior and behavior problems. Int J Offender Ther Comp Criminol. 2013;57:112–26.PubMedView ArticleGoogle Scholar
- Cooke DJ, Michie C, Hart SD, Clark DA. Reconstructing psychopathy: clarifying the significance of antisocial and socially deviant behavior in the diagnosis of psychopathic personality disorder. J Pers Disord. 2004;18:337–57.PubMedView ArticleGoogle Scholar
- Frick PJ, Cornell AH, Bodin SD, Dane HA, Barry CT, Loney RB. Callous- unemotional traits and developmental pathways to severe conduct problems. Dev Psychol. 2003;39:246–60.PubMedView ArticleGoogle Scholar
- Pardini DA, Loeber R. Special section: interpersonal and affective features of psychopathy in children and adolescents: advancing a developmental perspective. J Clin Child Adolesc Psychol. 2007;36:269–75.PubMedView ArticleGoogle Scholar
- Asgeirsdottir BB, Sigfusdottir ID. Gender differences in co-occurrence of depressive and anger symptoms among adolescents in five Nordic countries. Scand J Public Health. 2014. [Epub ahead of print].Google Scholar
- Logan C, Weizmann-Henelius G. Psychopathy in women: presentation, assessment, and management. In: Häkkänen–Nyholm H, Nyholm J-O, editors. Psychopathy and Law. A practitioner’s guide. Singapore: Wiley-Blackwell; 2012.Google Scholar
- Vitacco MJ, Rogers R, Neumann CS. The antisocial process screening device; an examination of its construct and criterion-related validity. Assessment. 2003;10:143–50.PubMedView ArticleGoogle Scholar
- Hopwood CJ, Donnelan BM. How should the internal structure of personality inventories be evaluated? Pers Soc Psychol Rev. 2010;14:332–46.PubMedView ArticleGoogle Scholar
- Cooke DJ, Michie C, Skeem J. Understanding the structure of the Psychopathy Checklist-Revised: an exploration of methodological confusion. Br J Psychiatry. 2007;190:S39–50.View ArticleGoogle Scholar
- Neumann CS, Kosson DS, Forth AE, Hare RD. Factor structure of the hare Psychopathy Checklist: Youth Version (PCL:YV) in incarcerated adolescents. Psychol Assess. 2006;18:142–54.PubMedView ArticleGoogle Scholar
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