criminal recidivism among juvenile offenders: testing the incremental and predictive validity of...
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Criminal Recidivism among Juvenile Offenders: Testing the Incremental and PredictiveValidity of Three Measures of Psychopathic FeaturesAuthor(s): Kevin S. Douglas, Monica E. Epstein and Norman G. PoythressSource: Law and Human Behavior, Vol. 32, No. 5 (Oct., 2008), pp. 423-438Published by: SpringerStable URL: http://www.jstor.org/stable/25144642 .
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Law Hum Behav (2008) 32:423-438 DOI 10.1007/sl0979-007-9114-8
ORIGINAL ARTICLE
Criminal Recidivism Among Juvenile Offenders: Testing the Incremental and Predictive Validity of Three Measures of Psychopathic Features
Kevin S. Douglas * Monica E. Epstein
*
Norman G. Poythress
Published online: 6 December 2007
? American Psychology-Law Society/Division 41 of the American Psychological Association 2007
Abstract We studied the predictive, comparative, and incremental validity of three measures of psychopathic features (Psychopathy Checklist: Youth Version [PCL:YV]; Antisocial Process Screening Device [APSD]; Childhood
Psychopathy Scale [CPS]) vis-a-vis criminal recidivism
among 83 delinquent youth within a truly prospective design. Bivariate and multivariate analyses (Cox propor tional hazard analyses) showed that of the three measures, the CPS was most consistently related to most types of recidivism in comparison to the other measures. However, incremental validity analyses demonstrated that all of the
predictive effects for the measures of psychopathic features
disappeared after conceptually relevant covariates (i.e.,
substance use, conduct disorder, young age, past property crime) were included in multivariate predictive models.
Implications for the limits of these measures in applied juvenile justice assessment are discussed.
Keywords Youth psychopathy Juvenile justice Risk assessment Prediction of recidivism PCL:YV:CPS:APSD
Despite declining rates of most types of criminal behavior
by adolescents in recent years (FBI Uniform Crime Reports
K. S. Douglas (El) Department of Psychology, Simon Fraser University, 8888 University Drive, Burnaby, BC, Canada V5A 1S6 e-mail: [email protected]
M. E. Epstein N. G. Poythress
University of South Florida, Tampa, FL, USA
2004, for rates between 1994 and 2003), it remains a
serious problem. In 2003, there was an estimated 1.3 mil lion arrests of juveniles (persons under 18) for criminal offenses (FBI Uniform Crime Reports 2004). Many of these were violent in nature (250,000+). Further, in recent
years the juvenile justice system has become increasingly punitive (Bonnie and Grisso 2000; Kupchik et al. 2003; Otto and Borum 2004). A concomitant need for risk assessment to differentiate low- and high-risk juvenile offenders has emerged. For this reason, a large amount of research has focused on identifying important risk factors for criminal and violent behavior among adolescents. One of the more commonly studied risk factors for criminal behavior is psychopathy. Most scholarship on psychopathy has been in the context of adult personality functioning, in which it is construed as a personality disorder consisting of behavioral tendencies (e.g., aggression, risk-taking behav
ior), affective deficits (e.g., callousness, shallow affect, lack of empathy), and interpersonal features (e.g., manip
ulativeness, dominance, grandiosity). There is ample evidence from adult-based research
demonstrating a link between psychopathy, typically as measured by the Hare Psychopathy Checklist-Revised
(PCL-R, Hare 1991, 2003) or its screening version, the Hare Psychopathy Checklist: Screening Version
(PCL:SV, Hart et al. 1995), and both general and violent recidivism. Meta-analyses have tended to show average
correlations approximately in the .25-30 range (for reviews and meta-analyses of the PCL-R and PCL:SV, see Douglas et al. 2006; Gendreau et al. 2002 [and Hemphill and Hare 2004, in rebuttal]; Guy et al. 2005; Hare 2003; Hemphill etal. 1998; Salekin etal. 1996; Walters 2003a, b), with some meta-analyses finding smaller effect sizes (rs = .16?.21) for violence (Gendreau et al. 2002; Guy et al. 2005).
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424 Law Hum Behav (2008) 32:423-438
The downward extension of the psychopathy construct to youth is a recent occurrence that is controversial on
developmental, theoretical, and conceptual bases (see Edens et al. 2001; Frick 2002; Johnstone and Cooke 2004;
Lynam 2002; Seagrave and Grisso 2002; Steinberg 2002).
Despite this, the pressing need in juvenile justice settings to
identify reliable risk factors for adolescent antisocial behavior has led researchers to study the relationship between psychopathic personality features and crime in
this age group. Studies tend to indicate that, regardless of
theoretical or developmental concerns, measures of youth
psychopathic features predict antisocial behavior with
meaningful effect sizes. For instance, Edens et al. (2001) concluded that, on average, there was a moderate associ
ation between various youth psychopathy measures and
relevant external criteria such as conduct disorder,
aggression, and impulsivity. Several contemporary measures of youth psychopathic
features have been developed, most notably the Hare
Psychopathy Checklist: Youth Version (PCL:YV; Forth et al. 1997, 2003), the Antisocial Process Screening Device
(APSD; Frick and Hare 2001), and the Childhood Psy
chopathy Scale (CPS; Lynam 1997). The Youth
Psychopathic Traits Inventory (YPI; Andershed et al.
2002), and the Psychopathy Content Scale (PCS; Murrie
and Cornell 2002) of the Millon Adolescent Clinical
Inventory (Millon 1993) are more recent additions to the
literature. Despite some variation, most studies show an
association between these measures and antisocial conduct.
For instance, many, though not all, studies using the PCL measures with youth (PCL-R, PCL-R modified for adoles
cents, or PCL:YV) indicate an association with criminal
history or institutional infractions (Brandt et al. 1997; Edens et al. 1999; Forth et al. 1990; Kosson et al. 2002; Murrie et al. 2004; Rogers et al. 1997; Salekin et al. 2004),
although there are exceptions (Campbell et al. 2004). In a
meta-analysis of 14 samples, Edens and Campbell (2007)
reported that the Hare psychopathy measures as applied to youth (18 and under) predicted institutional infrac
tions (physically violent and other aggressive incidents; rs =
22-25).
Fewer studies have been conducted of community recidivism. In a retrospective follow-up, youths who scored
high on the PCL: YV were three (violent recidivism) to four
(general recidivism) times more likely to recidivate than
those who scored low (Gretton et al. 2001). Gretton et al.
(2004) reported that the PCL:YV, completed retrospec
tively from files of adolescent offenders, predicted adult
criminally violent recidivism an average of 10 years post release. Further, in one of the few tests of the incremental
validity of the PCL:YV, Gretton et al. (2004) found that
file-only, retrospective PCL:YV ratings (total and Factor 2) remained significant after controlling for criminal history
and conduct disorder symptoms. In a smaller sample (N = 64) based on file-review PCL:YV ratings, O'Neill et al. (2003) reported moderate sized correlations between the PCL:YV and any recidivism. A further file-review
study of 95 adolescent offenders, however, found no rela
tionship between the PCL:YV and community recidivism
(Marczyk et al. 2003). Some studies have used the adult PCL-R modified for youths, and have reported similar
predictive findings (Brandt et al. 1997; Forth et al. 1990; Ridenour et al. 2001), although some have reported asso
ciations that are accounted for by other variables, such as
conduct disorder symptoms (Langstrom and Grann 2002). In one of the few truly prospective studies of the
PCL:YV for the purpose of predicting community recid
ivism, Corrado et al. (2004) followed 161 male
adolescents for 14.5 months after release from a youth detention facility in Canada. They reported that the
PCL:YV predicted any, violent, and non-violent recidi
vism, albeit with small to moderate effects (AUCs ranged from .58 to .68).1 In other analyses based on this sample, Vincent et al. (2003) reported, however, that a cluster
solution that comprised high scorers on all three factors
(interpersonal, affective, behavioral) had a significantly higher percentage of violent recidivists (approximately 50%) compared to cluster solutions consisting of high scorers on only one or two factors (23-27%). In another
community prospective study, Schmidt et al. (2006)
reported significant effects between the PCL:YV and
subsequent violent and general (though not non-violent) recidivism for 127 Canadian court-referred youths. How
ever, Edens and Cahill (2007) failed to observe significant
prediction of the PCL:YV for later community violent or
general recidivism.
Turning to the APSD, several studies?mostly using
parent and/or teacher ratings?have reported associations
between this measure and increased risk for aggression and
antisocial behavior in samples of clinic-referred and com
munity youth (Frick 1995; Frick et al. 2000a, b, 2003; Frick
and Hare 2001). Fewer studies have been reported for
justice-involved youth. In one such study of 69 arrested
youth, the correlations between the APSD and any recidi
vism (measured prospectively) were .32-36 for the self
report version, and .24-40 for the parent-report version
(.40 for total and impulsivity scales, .24 for callous
unemotional scale) (Falkenbach et al. 2003). Two studies
of institutional aggression reported significant correlations
(.25-35) with the APSD self-report version (Murrie et al.
2004; Spain et al. 2004). In the latter study, however, the
1 AUC stands for "area under the curve" of a receiver operating
characteristic analysis, with .50 representing chance prediction, and
1.0 representing perfect prediction.
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Law Hum Behav (2008) 32:423-438 425
APSD was no longer significant once the CPS was in the
predictive model. In the Spain et al. (2004) study, a modified version of
the CPS was more strongly and consistently related to
institutional infractions and violence than the APSD or
PCL:YV (being the only one of the three to retain signif icance in multivariate analyses), with bivariate correlations with the rate of any and violent infractions of .43 and .45,
respectively. In Falkenbach et al's (2003) study, the CPS had strong correlations with community recidivism when rated by parents (.40s-.50s), though smaller correlations when rated by self (.20s-.30s).
Across the studies reviewed, there is some support for the relationship between each measure and criminal recidivism. However, viewed as a whole, the literature on
the prediction of adolescent criminal recidivism with measures of psychopathic features remains limited. Few studies are prospective, and some that are (Brandt et al.
1997) have used the (modified) PCL-R rather than the PCL:YV per se. Many PCL:YV studies use file-only rat
ings, a nonfatal methodological characteristic to be sure,
but one that limits the comprehensiveness of the assess ment process and is known to lower scores and restrict
range (Hare 2003). Further, to our knowledge, there has yet to be a prospective comparison ofthe PCL:YV, APSD, and CPS for the prediction of community recidivism among adolescent offenders.
In addition, most studies have not gone beyond reporting the absolute magnitude of association between psychopa thy measures and recidivism to evaluate the incremental contribution of psychopathy measures once other relevant correlates are controlled, a procedure recommended for
testing their utility beyond other factors (Douglas et al.
2006; Edens et al. 2006). In a rigorous example of incre mental validity analysis from the adult psychopathy literature, Skeem and Mulvey (2001) showed a substantial reduction in the predictive validity (from a correlation of .26-. 12) of the PCL:SV Part 2, once numerous relevant
covariates were controlled via propensity analyses. How
ever, there are few such examples from the youth
psychopathy literature. Gretton et al. (2004) reported that the PCL:YV remained associated with later community recidivism after controlling for past criminality. Others have found that the PCL:YV added incrementally to indi ces of externalizing behavior and criminal history (Schmidt et al. 2006). Langstrom and Grann (2002), however, found that the PCL:YV was reduced to statistical nonsignificance once conduct disorder symptoms were entered into the
predictive model. As such, we selected several domains of risk factors
that, based on theory and past research, ought to predict criminal behavior among adolescents (see, generally, Cot tle et al. 2001; Corrado et al. 2002; Dahlberg and Simon
2006; Fried and Reppucci 2002). These domains included
(a) demographics (here, age); (b) past antisocial behavior
(i.e., past crime, antisocial behavior while incarcerated); (c) substance-related problems (i.e., drug and alcohol abuse and dependence); and (d) mental health problems (i.e., anger, conduct disorder). We were interested in whether the various measures of psychopathic features could pre dict recidivism above and beyond these risk factors; that is, do measures of psychopathy show predictive utility incre
mentally beyond common risk factors for antisocial behavior?
The present study was conducted to address these col
lective limitations of the research corpus. As some studies indicate that certain sub-scales are more strongly related to
antisocial behavior than others (in particular, the behav ioral components of the PCL:YV), we conducted tests of each measure's sub-scales as well. Finally, reflecting calls
in the literature to investigate multiple aspects of offend
ing behavior (Hart 1998), we evaluated not only the
relationship between the psychopathy measures and the occurrence of recidivism, but the nature of recidivism (i.e.,
violent, non-violent, weapons-related), time to recidivism,
and volume and diversity of recidivism. Given the value of an incremental validity approach generally (i.e., Sechrest
1963), and the small number of studies that have addres sed this issue for youth psychopathy measures vis-a-vis other risk factors theoretically related to antisocial
behavior, we also tested three measures of youth psy
chopathic features against each other, and alongside other
putative risk factors and demographics (age, previous antisocial behavior, mental health diagnoses and substance related problems).
Method
Participants and Setting
Ninety-six male adolescent offenders between the ages of 11 and 18 (M = 15.77, SD = 1.35) who were remanded to a secure facility located in west central Florida were recruited to participate in the study. Eleven residents declined. Of the 85 participants, 42 were enrolled in a Sex Offender Program (SOP) and 43 residents in a secure res idential Halfway House Program (HHP; e.g., nonsexual
offenders). Data from one SOP and one HHP participant were dropped from analyses due to incomplete measures,
leaving 83 participants for analysis. The sample was pri marily Caucasian (79%), while the remainder identified their race as African American (16%) or Latino (4.9%). Based on the Hollingshead (1975) Index, custodial socio economic status for the majority of the participants was lower to lower-middle class (M = 5.38, SD = 2.0). Length
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426 Law Hum Behav (2008) 32:423^38
of incarceration at the facility ranged from 186 to
1,110 days (M = 410.7, SD = 172.1).
Measures of Psychopathic Features in Youth
Hare Psychopathy Checklist: Youth Version (PCL.YV)
The PCL:YV is a 20-item, clinician-administered instru ment patterned after the adult PCL-R but designed to
evaluate psychopathic personality features in youth aged 12-17. Like the PCL-R, the PCL:YV relies on information
gleaned from interview, file review, and collateral infor mation. Scores range from 0 to 40, with each of the 20
items rated on a three-point (0-2) scale. The two-factor, four-facet model encompassing Factor 1 (Interpersonal and
Affective) and Factor 2 (Behavioral and Antisocial Fea
tures) was used in this study. We used the pre-published research version (Forth et al. 1997) although it does not
differ from the published version in terms of administration
procedure or item definitions (Forth et al. 2003).
Adequate psychometric properties of the PCL:YV have
been reported in several studies (see Edens et al. 2001; Forth and Burke 1998; Forth and Mailloux 2000; Kosson
et al. 2002; Vincent and Hart 2002). The PCL:YV manual
(Forth et al. 2003, p. 55) reports excellent interrater
agreement for the Total score (ICC = .90-92) across jus tice-involved youth in institutions, on probation, and in
clinic/community samples. Across various samples, inter
nal consistency for the Total score, as indexed by Cronbach's alpha (.85-94) and item homogeneity as
indexed by mean inter-item correlation (.23-43) are also
good. The PCL:YV manual also reports satisfactory inter nal consistency for the four-facet model, with alphas of .71
(Interpersonal), .72 (Affective), .68 (Behavioral), and .77
(Antisocial) in a sample of 505 incarcerated males (Forth et al. 2003, p. 65). In the present sample, alpha for the total
score, and facets 1-4, respectively, were .71, .53, .55, .43,
and .51.2 Means (SDs) for the total and facets (1-4) were,
respectively, 22.8 (5.9), 3.1 (1.9), 4.3 (2.1), 6.0 (1.9), and
7.0 (2.1). Ten paired ratings of PCL:YV administrations were
collected throughout the data collection period to assess
interrater reliability. Employing absolute agreement intra
class correlation (ICQ procedures for both single ratings
(ICCi) and averaged ratings (ICC2) across the 10 paired
ratings (see Bartko and Carpenter, 1976), acceptable
2 Other investigators have reported reliability based on the three
factor model. Lee et al. (2003) obtained as of .59, .63, and .44,
respectively, for the three factors (which are the same as the first three
of four factors used in the present research), whereas Vincent (2002) obtained as of .71, .67, and .60, respectively. Skeem and Cauffman
(2003) reported as of .57, .56, and .22, respectively.
ratings of ICCX = .82 and ICC2 = .90 were obtained for PCL: YV Total scores. Inter-rater reliabilities (/CCO for the
Interpersonal, Affective, Behavioral, and Antisocial sub scales were 0.86, 0.43, 0.83, and 0.61 respectively. One
highly discordant paired rating strongly affected the reli
ability coefficient of the Affective sub-scale such that its removal increased the coefficient to 0.71.
Antisocial Process Screening Device (APSD)
We employed the 20-item self-report version of the APSD that has been developed for research with youths 12 18 years old (see Caputo et al. 1999). The original measure
(Frick and Hare 2001) was designed for completion by parents or teachers; however, a self-report version was
created by changing the items from third-person ("He
keeps the same friends") to second-person ("You keep the same friends"). Frick et al. (2000a, b) noted "[s]elf-report becomes more reliable and valid as a child enters adoles
cence, especially for assessing antisocial tendencies and
attitudes that may not be observable to parents and other
significant adults" (p. 13).
Except for a study by Rogers et al. (2002), which
obtained an alpha of .58, internal consistency for the self
report Total score has been good, with alphas ranging from
.72 to .82 (mdn = .76) (Cruise et al. 2000; Lee et al. 2003; Murrie and Cornell 2002; Pardini et al. 2003). However, internal consistency has been modest to weak for the three
factor scores, ranging from .56 to .72 for Narcissism
(NAR; mdn = .68), .36-.56 for Callous-Unemotional (C-U; mdn = .52), and .44 to .60 for Impulsivity (IMP; mdn =
.56). We used the official factor structure reported in the
APSD manual (Frick and Hare 2001) for analyses. In the
present sample, alpha for the APSD total, NAR, IMP, and
C-U scales was .76, .69, .56, and .19, respectively.3 Mean
3 The low alphas, particularly for C-U, are consistent with the
literature, and likely not a function of this particular sample. In a
quantitative synthesis of APSD reliability estimates based on 11
samples and 1,253 participants, Poythress et al. (2006) reported median alpha values that were highly consistent with our estimates.
For the APSD NAR scale, the median alpha was .69 (in our sample, a = .69), for IMP it was .53 (in our sample, a = .56), and for the C-U
scale, it was .46 (in our sample, a = .19). Because of concern that low
internal consistency could reduce validity coefficients, we calculated
"reliability enhanced" versions of the APSD scales for some validity
analyses by removing the most poorly performing items from each
scale and sub-scale (validity results summarized in footnote 5). For
the sake of thoroughness, we also attempted to increase the reliability of each PCL:YV and APSD index. The largest increase in alpha was
associated with the C-U scale from the APSD, which increased from
.19 to .50 after removing items 19 and 20. Alpha for other APSD and
PCL:YV indices increased negligibly (range .01-06). We also note
that the removal of items 19 and 20 produces a revised factor model
tested and supported by Poythress, Dembo et al. (2006).
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Law Hum Behav (2008) 32:423-438 427
(SD) scores for the APSD total, NAR, IMP, and C-U scales were 16.1 (5.9), 5.1 (2.8), 5.0 (2.1), and 4.2 (1.8),
respectively.
Child Psychopathy Scale
The original version of the CPS had 41 items and was
intended to be rated by parents (Lynam 1997). It was
modified to include 55 items in a self-report format
(Lynam, personal communication). Each item is rated on a
2-point scale (0 = no, 1 = yes). Lynam (1997) reported excellent internal consistency (Cronbach's a = .91) for the
original CPS. Evidence for the construct validity of the measure was reflected through positive correlations (range .19-39) with various measures of delinquency and exter
nalizing problems, and negative correlations with indices
of internalizing problems. As the CPS does not have an
empirically-derived factor structure, we derived three fac tors rationally in consultation with the CPS author in order to facilitate comparisons with the APSD and PCL:YV. These rationally derived factors have been used in previous studies (Spain et al. 2004). In the present sample, alpha for the total, interpersonal, affective, and behavioral CPS scales were .87, .73, .68, and .71, respectively. Mean (SD)
scores for the CPS total, interpersonal, affective, and behavioral CPS scales were 5.31 (1.85), 1.85 (.63), 1.27
(.63), and 1.55 (.84), respectively.4
Measure Intercorrelations
The total scores for the psychopathy measures correlated with one another as follows: PCL:YV and APSD (r = .35, p < .01); PCL:YV and CPS (r = .27, p < .02); CPS and APSD (r = .79, p < .001). PCL:YV sub-scales produced correlations with the sub-scales on the APSD ranging from .04 (ns) between Facet 1 (Interpersonal) and APSD
Impulsivity, to .29 (p < .001) between Facet 2 (Affective) and APSD Narcissism. PCL:YV sub-scales correlated with the sub-scales of the CPS with a range of .05 (ns) between Facet 3 (Impulsivity) and CPS Interpersonal, to .34
(p < .001) between Facet 4 (Antisocial) and CPS Impul sivity. Correlations between APSD and CPS sub-scales
ranged from .35 (p < .001) between APSD C-U and CPS
Interpersonal to .62 (p < .001) between APSD Narcissism and CPS Affective.
As the CPS sub-scales were rationally derived, we
provide additional detail on the correlations between its three 'scales' and the corresponding scales on the APSD
Scale scores on the CPS are the means of item scores, hence their low magnitudes.
and PCL:YV. CPS Interpersonal correlated with the cor
responding PCL:YV scale (Facet 1) at .22 (p < .05), and the APSD scale (Narcissism) at .54 (p < .001). Its Affec tive scale correlated with PCL:YV Facet 2 at .25 (p < .03) and APSD C-U at .38 (p < .001). Finally, its Impulsivity scale correlated with the PCL:YV Facet 3 (Impulsivity) at
.24 (p < .05), PCL:YV Facet 4 (Antisocial) at .34
(p < .01), and APSD Impulsivity at .60 (p < .001). These cross-measure correlations indicate at least preliminary evidence of concurrent validity of the rationally derived scales of the CPS.
Covariates
Mini-International Neuropsychiatric Interview
for Children and Adolescents (MINI-Kid)
The MINI-Kid (Sheehan et al. 2001) was used to assess
selected DSM-IV Axis I disorders (e.g., generalized anxiety, major depressive episode, conduct disorder), including alcohol and substance abuse/dependence. A full day of
training was provided to the authors by one of the authors of the MINI-Kid. The instrument is a brief diagnostic struc tured interview designed to meet the need for a short but accurate psychiatric assessment. The MINI-Kid is a
downward version of the adult Mini-International Neuro
psychiatric Interview (MINI; Sheehan et al. 1997) that frames questions in language that is easy for children and adolescents to understand. Most prompts can be responded to by "yes" or "no," and limited clinical judgment is
required to complete the assessment. The adult MINI diag nostic concordance with the Structured Clinical Interview for DSM-III-R Diagnosis (SCID) has reported kappas ranging between .50 and .90 for each disorder assessed (with one exception: Current drug dependence kappa
= .43).
Sensitivity was greater than .70 for all but three values
(dysthymia, OCD, and current drug dependence); specificity and negative predictive values (NPV) were 0.85 or higher across all diagnoses; and positive predictive values (PPV) ranged from 0.45 to 0.75, suggesting that it is a valid measure of eliciting symptom criteria used to make DSM-IV diag noses. The MINI-Kid has been used in studies of Tourette's
syndrome (Silver et al. 2001) and the impact of residential
placement on pharmacotherapy with youths (Bastiaens 2004). Although the MINI-Kid is modeled directly after
MINI, to date, no studies of its psychometric properties have been published. Unfortunately, we do not have interrater
reliability data from this sample. For incremental validity analyses, we used indices from
the MINI-Kid with a conceptual relationship to crime and violence?alcohol and drug-related disorders (diagnoses for alcohol abuse and dependence, drug abuse and
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428 Law Hum Behav (2008) 32:423^138
dependence, and substance abuse and dependence), con
duct disorder, and attention-deficit hyperactivity disorder. When possible (i.e., for those disorders for which the MINI-Kid permits it), we used symptom counts rather than dichotomous diagnostic indications (conduct disorder;
ADHD).
The Massachusetts Youth Screening Instrument-Second
Version (MAYSI-2)
The MAYSI-2 (Grisso et al. 2001) is a self-report inventory designed to screen 12-17 year-old youth in juvenile justice facilities who may have special mental health needs (Grisso and Barnum 2000). Youths respond "yes" or "no" to each of 52 items regarding their thoughts, feelings, and behaviors "within the past few months." These items contribute to seven factor analytically-derived scales representing prob lem areas. Although the entire measure was administered,
only two scales were included in the present analyses: Alcohol/Drug Use (8 items: e.g., "Have your parents or
friends thought you drink too much?"), and Angry-Irritable (9 items: e.g., "Have you felt angry a lot?").
Norms for the MAYSI-2 were developed on a sample of
1,279 youths, aged 12-17 inclusive, recruited through various juvenile justice agencies in Massachusetts during 1997. Coefficient alpha values were >.70 for all scales in
the normative sample except for two (Thought Disturbance a = .61, and Trauma Experience (boys) a = .63). Internal consistencies for the MAYSI-2 factors used in this
study were as follows: Alcohol/Drug Use, a = .88; Angry Irritable, a = .82.
Past Antisocial Behavior
We used two indices of past crime?crimes against persons
and crimes against property (each coded dichotomously).
Fifty-three participants (62.4%) had previous crimes
against persons, and 54 (63.5%) had previous crimes
against property. We also calculated two rate variables:
prior offending (number of crimes divided by age at
admission) and institutional infractions (number of insti
tutional infractions divided by time in program). Past crime was coded from official juvenile justice records maintained
by the Florida Department of Juvenile Justice.
We categorized the covariates above into four catego
ries: (a) mental health problems (conduct disorder; MAYSI-2 Angry-Irritable; ADHD), (b) substance-related
problems (substance-related diagnostic variables; MAYSI
2 Alcohol/Drug Use), (c) prior antisocial behavior (past
property crimes; past person crimes; rates of past crime and
institutional infractions), and (d) age at discharge.
Outcome Recidivism Data
Recidivism was coded from official Florida DJJ records. We classified formal contacts (charges and convictions) into the following dichotomously scored recidivism cate
gories: (a) any; (b) violent; (c) non-violent; and (d) weapons. A violent offense was defined as any that involved actual or potential harm to persons, including assault, assault with a weapon, or robbery. Most violent
offenses were assaults. Note that these categories are not
mutually exclusive, but are intended to describe different
types of recidivism. Any recidivism is a summary category that was coded positive for any post-release formal contact.
This index was divided into (mutually exclusive) catego ries of violent and non-violent recidivism. Weapons-related offenses are not independent of the other offense catego ries, but could appear in either the violent or non-violent
category depending on the nature of the charge (i.e., simple possession was considered non-violent; assault with a
weapon was considered violent). These more detailed
categories were created to address the specificity of recidivism in which participants might be involved. We observed the following recidivism base rates (all/83): (a)
any (n = 37; 44.6%); (b) violent (n = 19; 22.9%); (c) non
violent (n = 32; 38.6%); and (d) weapons (n = 6; 7.2%). In order to test whether the psychopathy measures pre
dicted not only recidivism per se, but serious repeat recidivism, or "high volume" offending, we first calculated
the total number of re-offenses committed by the cohort of
participants, which was 179. Approximately 10% of the
sample (8 youths) committed well over half of these offenses (n = 109; 60.9%; range = 8-21 offenses). We
then created a dichotomous variable (participant was [1] or was not [0] among the 10% of high-volume offenders) and used this as the dependent variable for a subset of analyses.
We also calculated the number of offense types that
participants engaged in as an index of their diversity of
offending. For this one analysis, we summed across four
independent types of offenses: violent offenses, property offenses, breaches, and drug-related offenses. Hence this
index could range from 0 to 4. Because it was a highly skewed variable, analyses used a natural logarithmic transformation. Note that for all other analyses, property, breach, and drug-related offenses were subsumed under the
'non-violent offense' category.
We attempted to allow approximately 1 year post
discharge prior to collecting recidivism data to increase the
probability that crimes that were actually committed had
time to be processed and entered into the official DJJ
database. The minimum follow-up time was 310 days; the
maximum was 1,282 days. The mean number of days
between discharge and the date that we requested recidi
vism data was 874.77 (SD = 223.27; Mdn = 912).
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Law Hum Behav (2008) 32:423-438 429
Procedure
Graduate level clinical research assistants were trained on
protocol administration in a 2-day workshop. Training for PCL:YV administration included didactic presentations on
the psychopathy construct and a review of differences between the adult and youth versions of the PCL. Research assistants also completed scoring of videotaped PCL-R
interviews with feedback from supervisors. There were two
graduate students who collected most of the data (65
cases). One graduate student had to stop involvement with the project after two cases. The remaining 17 cases were
collected by the two faculty involved in the project (8 and 9
cases, respectively). Participants were recruited using methods approved by the University of South Florida's Institutional Review Board and the Florida Department of Juvenile Justice Institutional Review Board. Assent from
each participating adolescent was obtained and parents or
guardians were informed of the study by a letter that
explained that they could exclude their child from the study by contacting the investigators (passive consent). Assent for voluntary participation was obtained face-to-face dur
ing recruiting interviews with youths who were provided a
description of the study and afforded an opportunity to ask
questions. These same research assistants returned to the
facility at a later date to administer the single-session, 2-3 h protocol to those residents who had given prior assent. The PCL:YV ratings were based on data from institutional and juvenile justice files as well as the PCL:YV semi-structured interview.
Analyses
Bivariate Analyses
We used Receiver Operating Characteristic (ROC) anal
yses as the primary index of predictive accuracy at the bivariate level. ROC analysis can be used to estimate
predictive accuracy when there is a continuous predictor and a dichotomous outcome. The effect size that it yields, called the Area under the Curve (AUC), is not greatly attenuated by deviations from base rates of 50% in the outcome variable of interest (here, recidivism) (Mossman 1994). "Receiver operating characteristic" analysis is so
named because the "receiver" of the data (the researcher or clinician) can "operate" (make decisions) at any given point on the curve (Metz 1978), hence understanding its
predictive "characteristics" across the whole range of
scores. The curve produced by ROC analysis is a func tion of the plotting of sensitivity (true positive rate
[TPR]) of the predictor against the false positive rate
(FPR [1-specificity]) (Mossman and Somoza 1991). At
any and all levels of sensitivity, the "receiver" knows the
specificity. The AUC, an index of overall predictive accuracy,
ranges from 0 (perfect negative prediction), to .50 (chance
prediction), to 1.0 (perfect positive prediction). The AUC is the probability that a randomly chosen person who scores
positive on the dependent measure (in this case, is actually violent) will score higher than a non-violent person on the
predictor measure (Mossman and Somoza 1991). Although there would seem to be no general agreement in the area of risk assessment regarding what values of AUC represent small, moderate, or large effect sizes, formulae from
Dunlap (1999) indicate that an AUC value of .71 corre
sponds to a standardized difference score (d) of .80, which was suggested by Cohen (1992, 1988) to represent an effect of large magnitude. An AUC value of .64 corresponds to a
d of .50 (moderately sized effect). Because follow-up times varied greatly across partici
pants, we chose a uniform follow-up period for these
analyses. The minimum follow-up time (310 days) was
met by the entire sample. However, limiting the measure ment of recidivism to this time period resulted in low base rates for violent recidivism (<10%), one of the main out come indices, and hence would not have provided a
reasonable test of the measures' predictive accuracy. We
were able to retain approximately 90% of the sample (n = 71) with a uniform follow-up of 620 days. Using this
follow-up period, the base rates of the main outcome cri
teria were high enough to justify analyses: any (40.9%); violent (25.4%); and non-violent (36.6%). The base rate for
weapons-related recidivism was low (5.6%), and hence we
recommend caution in interpreting those particular analyses.
Multivariate Analyses
Because we had uneven follow-up periods across partici
pants, survival analysis was used as the primary multivariate procedure. "Survival analysis" is the term
applied to a cluster of analyses that uses time to an event as the dependent measure, models the time to an event, and
controls for unequal follow-up times between participants (Luke and Homan 1998). Survival analysis also permits the evaluation of changes in the hazard function (rate of fail
ure) as a function of relevant covariates. Specifically, the Cox proportional hazards model?a semi-parametric pro
cedure that allows evaluation of how numerous categorical or continuous covariates affect the hazard rate of the
dependent variable?was used. The procedure is semi
parametric because it does not model the shape of the hazard function, but it does model the effects of covariates on the hazard function (Luke and Homan 1998). The Cox
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430 Law Hum Behav (2008) 32:423-438
proportional hazards model also provides estimates of the
magnitude of effect of covariates, an advantage over other
survival procedures, such as the Kaplan-Meier method.
Results
Bivariate Relationship between Youth Psychopathy Measures and Criminal Recidivism
For informational purposes, we first report AUCs that were
significant at a traditional alpha level of .05 (the details of
non-significant AUCs are available upon request). However,
as there was a large number of significance tests conducted, we applied an alpha correction procedure for interpretive purposes. Each psychopathy index was tested against four outcome criteria, and hence we set alpha for interpretive purposes to .05/4 = .0125. A summary ofthe indices which met this more conservative alpha level is presented after a
report of those that met the traditional alpha level.
PCL:YV total score did not significantly predict the any outcome criterion (AUC = .55, SE = .07, 95% CI = .42
.69, ns) or the non-violent outcome criterion (AUC = .50,
SE = .07, 95% CI = .36-.63, ns). However, it was signif
icantly related to both violent recidivism (AUC = .66, SE = .07, 95% CI = .52-/79,/? < .05) and weapons-related recidivism (AUC = .81, SE = .05, 95% CI = .71-.91,
p < .05). The APSD total score followed the same pattern, in that
it did not significantly predict the any outcome criterion
(AUC = .63, SE = .07, 95% CI = .50-.76, ns) or non
violent recidivism (AUC = .58, SE = .07, 95% CI = .45
.72, ns). However, it was significantly predictive of violent
recidivism (AUC = .69, SE = .07, 95% CI = .55-.83,
p < .02) and weapons-related recidivism (AUC = .90, SE = .04, 95% CI = .82-.98, p < .01).
The CPS total score predicted any recidivism (AUC =
.67, SE = .06, 95% CI = .55-.80, p
= .01), non-violent
recidivism (AUC = .64, SE = .07, 95% CI = .51-/77,
p < .05), violent recidivism (AUC = .70, SE = .07, 95%
CI = .57-84, p =
.01), and weapons-related recidivism
(AUC = .83, SE = .13, 95% CI = .58-1.1, p < .05).
Turning to the measures' sub-scales, none of the
PCL:YV facets were predictive of the any outcome crite
rion (AUC range = .52-62) or non-violent recidivism
(AUC range = .45-62). For violent recidivism, Facet 4
(AUC = .65, SE = .07, 95% CI = .51-.80, p = .05) was
predictive, and for weapons-related recidivism, only Facet
2 (Affective) was predictive (AUC = .84, SE = .05, 95%
CI = .74-.95, p =
.02).
Of the APSD sub-scales, only IMP predicted the any outcome criterion (AUC = .64, SE = .07, 95% CI = .51
.77, p < .05). None of the sub-scales were significantly
predictive of non-violent recidivism (AUC range = .54
.61). For violent recidivism, both NAR (AUC = .70, SE = .07, 95% CI = .56-.84, p = .01) and IMP (AUC =
.70, SE = .07, 95% CI = .57-.83, p = .01) were signifi cantly predictive. Similarly, both NAR (AUC = .80, SE = .09, 95% CI = .63-.98, p < .05) and IMP (AUC =
.89, SE = .05, 95% CI = .81-.98, p < .01) were signifi cantly predictive of weapons-related recidivism.
Finally, for CPS sub-scales, both the Interpersonal and
Behavioral/Impulsivity factors were predictive of each type of outcome, whereas the Affective factor did not predict any of the outcomes. The Interpersonal (AUC = .66, SE = .07, 95% CI = .53-.79, p = .02) and Behavioral/Impulsivity factors (AUC = .68, SE = .07, 95% CI = .55-.81, p = .01) were predictive of the any outcome criterion. Similarly, they were predictive of violent recidivism (Interpersonal AUC = .67, SE = .07, 95% CI = .53-.81, p < .05; Behav
ioral AUC = .73, SE = .07, 95% CI = .58-.87, p < .005), non-violent recidivism (Interpersonal AUC = .66, SE =
.07, 95% CI = .53-.79, p < .05; Behavioral AUC = .66, SE =
.07, 95% CI = .53-.80, p < .05), and weapons
related recidivism (Interpersonal AUC = .80, SE = .12, 95% CI = .56-1.0, p < .05; Behavioral AUC = .83, SE =
.07, 95% CI = .68-.97, p < .05). At the more conservative alpha level of .0125, the
PCL:YV total score was not significantly related to any outcome. The APSD total score was significantly predic tive only of weapons-related recidivism. The CPS total score was significantly predictive of any and violent
recidivism. None of the PCL: YV sub-scales met this more
conservative alpha level. APSD NAR and IMP were sig nificantly predictive of violent recidivism, and NAR was
predictive of weapons-related recidivism as well. CPS
Behavioral/Impulsivity was predictive of any recidivism and violent recidivism.5
High-Volume and Diverse Offending
As it was not possible to use a uniform follow-up period for
these analyses (we did not record the date of every offense,
just that of the first offense), instead of AUC analyses, we
used partial correlational analyses, controlling for time at
5 Owing to the concern that the low reliability of some of the scales
could have reduced the predictive validity of these scales, we
conducted additional ROC analyses (for any, violent, and non-violent
re-offenses) for the APSD and PCL:YV using the "reliability enhanced" sub-scales described in the Methods section. For the
PCL:YV tests, AUC values increased, on average, by .007. For the
APSD, the mean change was -.001. Overall, our evaluation of these
changes was that they were minimal and did not warrant further
investigation (i.e., in the multivariate analyses) or substitution of the
reliability enhanced scales for the original scales throughout all
analyses.
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Law Hum Behav (2008) 32:423-438 431
risk. As with the previous bivariate analyses, we first report
analyses based on alpha = .05. We then provided a sum
mary of which indices remained significant using a more
conservative alpha to correct for multiple tests. For this set
of analyses, each index was used to predict two outcomes, and hence we set this more conservative alpha at .025.
Of the total scores, the PCL: YV predicted neither high volume nor diverse recidivism, the APSD predicted
diversity of offending (partial r - .24, p = .03), and the
CPS predicted both high-volume (partial rpb = .25,
p = .02) and diverse offending (partial r = .28, p = .01). The only PCL:YV sub-scale that was predictive of either
index was Facet 4 (Antisocial) (partial rpb = .23, p = .04)
with respect to high-volume offending. The only APSD
sub-scale that was predictive was IMP with respect to
diverse offending (partial r = .25, p = .02). Finally, for the
CPS, both the Interpersonal and Behavioral sub-scales
predicted both high-volume (Interpersonal partial rpb =
.27, p = .0V, Behavioral partial r = .24, p
= .03) and
diverse recidivism (Interpersonal partial rpb = .29, p < .01;
Behavioral partial r - .29, p < .01).
The analyses that met the more conservative alpha level of .025 included the following: CPS total score for both
high-volume and diverse offending; APSD IMP for diverse
offending; CPS Interpersonal for both high-volume and
diverse offending; and CPS Behavioral for diverse
offending.
Multivariate Relationship between Youth Psychopathy Measures and Criminal Recidivism
We conducted multivariate analyses to discern which of the three psychopathy measures was independently predictive of each type of outcome. We used Cox proportional hazard
analysis, which models time to event as the outcome. Two
primary sets of analyses were conducted?first for the measures' total scores, and second for the measures' sub
scale scores. For the sub-scale analyses, we first conducted
analyses within-scale to determine which of each mea sures' sub-scales was independently related to recidivism.
Then, we pitted these sub-scales against one another in a
further series of analyses. We performed this two-step
procedure with the sub-scales because with an N of 83 and 10 sub-scales across measures, entering all sub-scales into
one Cox regression analysis would have underpowered the
analysis. All analyses used the forward conditional variable
entry method.
In terms of the total score analyses, Table 1 presents the measures that were significantly and independently pre dictive of the different categories of re-offending. As can be
seen, three recidivism variables were significantly pre dicted: any recidivism (CPS), violent recidivism (APSD),
and weapons-related offenses (APSD). Full model details
are presented in the Table 1. Notably, the PCL:YV was not
predictive of any outcome. With respect to sub-scale anal
yses, the results are presented in Table 2.6 As is evident, the
CPS (sub-scales) were most consistently related to the
various recidivism indices, with the APSD (Impulsivity)
being related only to weapons-related offenses. Again, the
PCL:YV was not predictive of any outcome.
Incremental Validity Analyses
Ofthe 15 covariates that we hypothesized would be related to recidivism, only 2 were unrelated to any of the recidi vism outcomes (rate of institutional infractions; rate of pre confinement offending), and hence these were dropped from all subsequent analyses. Given our moderate sample size, we adopted a sequential incremental validity analysis
procedure that minimized the number of covariates in any
given analysis. In Step 1, we identified each covariate that
had a bivariate relationship with any of the types of
recidivism that were significant in multivariate analyses (any; violent; non-violent; weapon-related). In Step 2, we
tested these covariates within their categories (past anti
social behavior; substance-related problems; mental health
problems) in a series of multivariate analyses (Cox
regression) using each relevant recidivism outcome as the
dependent measure. We did this to identify the covariates within categories that were independently related to the various types of recidivism. On Step 3, we used only those
covariates from Step 2 in incremental validity analyses with the psychopathy indices that we previously identified as being independently related to recidivism (i.e., those
reported in Tables 1 and 2). As young age was related to
each type of recidivism, it was included in all incremental
validity analyses as well. Most incremental validity anal
yses involved four covariates, which is a reasonable
number in terms of power, given our sample size. Typi
cally, one covariate from each category was represented in
these analyses, as described below.
The following sets of covariates, then, were used in incremental validity analyses, for the following recidivism outcomes: any and violent (young age; past property offenses; alcohol abuse diagnosis; conduct disorder
6 The following sub-scales were tested against one another for the
following types of recidivism, depending on whether they were
significantly predictive of recidivism in the first series of sub-scale
Cox regression analyses (i.e., those conducted within each measure
with just its own sub-scales): any (APSD Impulsivity; CPS Impul
sivity); violent (APSD Narcissism; PCL:YV Behavioral [Facet 3,
p < .10]; CPS Impulsivity); non-violent (CPS Interpersonal); and
weapons-related (APSD Impulsivity; PCL:YV Affective; CPS Impul sivity). Full details of this series of analyses are available upon request.
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432 Law Hum Behav (2008) 32:423^38
Table 1 Final Cox proportional hazard analysis models for total scores of psychopathy measures
Criterion/Predictor B SE (B) Wald eB (95% CI) Sig. Model cp
Any recidivism3
CPS .207 .088 5.498 1.231 (1.035-1.464) .019 .26
Violent recidivism5
APSD .088 .038 5.502 1.092 (1.050-1.425) .019 .26
Weapons-related recidivism0
APSD .165 .067 5.996 1.180(1.034-1.346) .014 .28
Note: Only the variables that were significant in final models are presented. The Model (p in the right-most column is a phi coefficient derived
from the overall model X2 calculated from the formula cp = yJ(X2/N) provided by Rosenthal (1991). It is provided as an effect size estimate of the
overall strength of the predictive model a Model -2LL = 291.51, X2 (df
= 1, N = 82) = 5.57, p < .05 b Model -2LL = 156.63, X2 (df= I, N = 82) = 5.56, p < .05
c Model -2LL = 46.02, x2 (df= \,N = 82) = 6.46, p < .01
Table 2 Final Cox proportional hazard analysis models for sub-scale scores of psychopathy measures
Criterion/Predictor B SE (B) Wald eB (95% CI) Sig. Model cp
Any recidivism3
CPS impulsivity .469 .187 6.317 1.599 (1.109-2.306) .012 .28
Violent recidivism13
CPS impulsivity .654 .252 6.723 1.924(1.173-3.155) .010 .29
Non-violent recidivism0
CPS interpersonal .674 .295 5.236 1.962 (1.102-3.495) .022 .25
Weapons-related recidivism41
APSD impulsivity .672 .254 6.985 1.957(1.190-3.221) .008 .32
Note: Only the variables that were significant in final models are presented. The Model cp in the right-most column is a phi coefficient derived
from the overall model X2 calculated from the formula (p = j(X2/N) provided by Rosenthal (1991). It is provided as an effect size estimate of the
overall strength of the predictive model a Model -2LL = 291.05, x2(df=l,N
= 82) = 6.37, p < .05 b Model -2LL = 155.32, X2 (df= 1, N = 81) = 6.90, p < .01
0 Model -2LL = 251.60, X2 (df= 1, N = 82) = 5.27, p < .05
d Model -2LL = 34.73, x2 (df= 1, N = 79) = 8.14, p < .005
symptom count); non-violent (young age; past property offenses; alcohol abuse diagnosis; MAYSI alcohol/drug use factor; conduct disorder symptom count); weapons
related (young age; past property offenses; substance
dependence diagnosis; conduct disorder symptom count). As is evident, some covariates were consistently related to
recidivism?young age, conduct disorder symptoms, alcohol abuse diagnosis, and past property offenses.
Our strategy was to extend the Cox regression analyses summarized in Tables 1 and 2 by adding the sets of
covariates, as single blocks, described in the previous
paragraph, in the first step of each Cox regression analysis (one for each recidivism outcome), and then entering the
relevant psychopathy scale or sub-scale. Incremental
validity was evaluated by whether the psychopathy index
added significantly to the covariates.
As is evident from Tables 3 (analyses involving total scores of psychopathy measures) and 4 (analyses involving
sub-scale scores of psychopathy measures), none of the
psychopathy indices added incrementally to the first step of
analyses involving the covariates only. Further, with
respect to the weapons-related recidivism outcome, despite
there being a significant overall model, neither of the
variables in the models retained individual levels of sig nificance. For the total score analysis, these variables were
conduct disorder symptoms (p = .09) and APSD Total
(p =
.23). For the sub-scale analyses, these variables were
conduct disorder symptoms (p = .07) and APSD Impul
sivity (p = .19).
Effect of Sub-Sample
As noted in the Methods section, our sample was approx
imately evenly divided between sexual offenders and non
sexual (general) offenders. This raises the question of
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Law Hum Behav (2008) 32:423-438 433
Table 3 Final incremental Cox proportional hazard analysis models for total scores of psychopathy measures
Criterion/Predictor B SE (B) Wald eB (95% CI) Sig. Model q>
Any recidivism3
Young age -.462 .144 10.298 0.630(0.475-0.835) .001 .65
Past property offenses 1.210 .460 6.920 3.353(1.361-8.261) .009
Alcohol abuse 1.187 .564 4.428 3.277(1.085-9.898) .035
Violent recidivism5
Young age -.506 .204 6.131 0.603(0.404-0.900) .013 .60
Alcohol abuse 2.142 .590 13.178 8.513 (2.679-27.057) .001
Note: Only the variables that were significant in final models are presented. The Model <p in the right-most column is a phi coefficient derived
from the overall model #2 calculated from the formula (p = ^/(/2/N) provided by Rosenthal (1991). It is provided as an effect size estimate ofthe
overall strength of the predictive model a Model -2LL = 264.57, x2 (df= 4, N = 80) = 33.46, p < .001
b Model -2LL = 140.31, %2 (df= 3, N = 82) = 29.93, p < .01
whether offender type influenced findings, in terms of the
relationship between predictors and outcomes. There is some reason to suspect that it might have, in that offender
type correlated with some of the predictor and outcome measures. In terms of psychopathy measures, offender
status (general offender) correlated with PCL:YV Facet 2
(rpb = .24, p < .05), Facet 3 (rpb
= .34, p < .01), and CPS
Total (rpb = .23, p < .05) and Behavioral (rpb
= .31,
p < .01) scores. It correlated with any (cp = .24, p < .05), violent (cp = .34, p < .01), and non-violent recidivism
(cp = .28, p < .05).
It is also important to note that in a logistic regression analysis we could account for 66% of the variance in offender status with the set of covariates used in the incremental validity analyses (-2LL = 57.83, df=6,
N - 82, Nagelkerke R2 = .66). Given this high correspon dence between offender status and the covariates, we ran
sets of hierarchical Cox regression analyses to test whether offender status added anything beyond the covariates in
predicting outcomes. We used the covariate sets shown in
the Tables (psychopathy total score analyses) for any, violent, and non-violent recidivism, entering the covariates
listed as the first block, and offender status as the second block. Offender status failed to enter any of the analyses, suggesting that it did not add to the covariates' predictive power vis-a-vis recidivism (details available upon request). For this reason, we did not run additional analyses with offender status as a separate covariate in addition to the more substantively meaningful covariates.
Nonetheless, it is of interest to test whether offender status (essentially a proxy for a more serious history of
offending, substance use problems, and conduct disorder) moderates the association between the psychopathy indices and outcomes. That is, does psychopathy predict recidi vism at the same strength for sex offenders and general offenders? We tested whether the psychopathy-outcome
relationships depicted in Table 1 (psychopathy total score
analyses) were moderated by offender status in a series of
hierarchical Cox regression analyses. On the first block of each analysis, we entered the relevant psychopathy index
plus offender status, and on the second block we entered the interaction between the two. We were interested in whether the interaction term was able to enter the model, based on a statistically significant improvement to model fit. Results indicated that only the CPS-Any recidivism
relationship was moderated by offender status, such that the strength of association between the CPS and any recidivism was stronger for general offenders (details available upon request).
Discussion
This was the first truly prospective study that we are aware
of that has contrasted the predictive validity of the
PCL.YV, APSD, and CPS, and one of the few studies within the youth psychopathy area to include analyses of the incremental validity of psychopathy beyond other
putative risk factors. Given the increasing use of these instruments in clinical decision-making, and the heightened debate about youth psychopathic features generally, this
type of research is necessary to understand the potential
predictive utility?and limits?of these measures.
Findings for the PCL: YV were perhaps surprising, given past studies that have supported its relationship to violence and antisocial behavior among delinquent samples (Gretton et al. 2001, 2004), albeit some with small or moderate effects (Corrado et al. 2004; Vincent et al. 2003), and others with nonsignificant results (Edens and Cahill 2007;
Marczyk et al. 2003). In the present study, even in bivar iate analyses the PCL:YV (total score and sub-scales) was not significantly related to recidivism when judged against
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434 Law Hum Behav (2008) 32:423^138
Table 4 Final incremental Cox proportional hazard analysis models for sub-scale scores of psychopathy measures
Criterion/Predictor B SE (B) Wald eB (95% CI) Sig. Model <p
Any recidivism3
Young age -.445 .143 9.720 0.641 (0.485-0.848) .002 .65
Past property offenses 1.190 .459 6.717 3.287(1.337-8.086) .010
Alcohol abuse 1.249 .562 4.944 3.488(1.16-10.490) .026
Violent recidivism15
Young age -.504 .208 5.884 0.604(0.402-0.908) .015 .61
Alcohol abuse 1.938 .582 11.102 6.946(2.221-21.722) .001
Non-violent recidivism0
Young age -.413 .143 8.291 0.662(0.499-0.876) .004 .63
Past property offenses .994 .505 3.879 2.703(1.005-7.272) .049
Alcohol abuse 1.354 .573 5.573 3.872(1.258-11.915) .018
Note: Only the variables that were significant in final models are presented. The Model (p in the right-most column is a phi coefficient derived from the overall model y1 calculated from the formula cp = ^/(^/N) provided by Rosenthal (1991). It is provided as an effect size estimate ofthe overall strength of the predictive model a Model -2LL = 264.10, f (df= 4, N = 80) = 34.08, p < .001
b Model -2LL = 139.74, x2 (df= 3, N = 80) = 29.88, p < .001
c Model -2LL = 228.77, jr2 (df= 4, N = 79) = 31.02, p < .001
a more conservative alpha level of .0125. In one of the other prospective studies of the PCL:YV, Vincent et al.
(2003) observed small to moderate effect sizes (AUCs =
.58-64), which overlap with and only slightly surpass those in the present study. Edens et al. (2007) observed AUCs that (save one) did not differ from chance in another
prospective study. The predictive validity of the self-report measures was
better than for the PCL:YV. In particular, the CPS was the most consistent predictor of recidivism in bivariate and non
incremental multivariate analyses. For instance, the CPS total score and Behavioral sub-scale remained predictive of
any and violent recidivism in bivariate analyses when
judged against the more conservative alpha. The CPS and its sub-scales also were the most consistently related to
high-volume and diverse offending. Both APSD NAR and IMP were predictive of violent recidivism in these bivariate
analyses. The APSD total score remained significantly related to weapons-related offenses when judged against the more conservative alpha. These findings build upon other
research using self-report methods that have shown rela
tionships with antisocial behavior, much (i.e., Frick et al.
2003; see Frick and Hare 2001, generally) though not all
(i.e., Falkenbach et al. 2003) of which has been with
community or clinic samples, by using a prospective design, a juvenile justice sample, and the CPS as well as the APSD.
It is of some interest to note which specific sub-scales of measures were related to recidivism in bivariate and non
incremental multivariate analyses. Behavioral features of
psychopathy tend to outperform the interpersonal and
affective features in terms of their relationship to general
criminal recidivism, although for violent recidivism, with some exceptions (Skeem and Mulvey 2001), interpersonal and affective features also tend to predict violence (for a
summary, see Douglas et al. 2006). Consistent with past research, in the present study, it was primarily behavioral sub-scales (impulsivity) that predicted recidivism (includ
ing violent recidivism), although the CPS Interpersonal scale entered one analysis.
Despite some promise of the self-report measures at the bivariate and non-incremental multivariate levels, these measures fared poorly in incremental validity analyses. Commentators in the psychopathy field (Douglas et al.
2006; Edens et al. 2006), drawing from more general, classic sources (Sechrest 1963), have highlighted the
importance of incremental validity analyses. It is important to know whether a construct adds anything beyond other
theoretically or empirically important variables in terms of
predicting outcomes. The present incremental analyses
provided no support for the incremental validity of the CPS or APSD in terms of their unique predictive strength vis-a vis recidivism once a small set of covariates was included
in predictive models (and the PCL:YV did not make it into
the incremental validity stage of analyses). This poor per formance in incremental validity analyses should temper any enthusiasm for such measures as providing unique information that is useful for prediction in the juvenile
justice system.
The covariates that reduced the predictive strength of the psychopathy measures in most analyses generally are
well known in the criminological and juvenile delinquency literatures. The current findings simply confirm that factors
^ Springer
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Law Hum Behav (2008) 32:423-438 435
such as serious substance related problems and previous crime are robust risk factors (Farrington 2002). The novelty of the present research was to test measures of another
putatively robust risk factor?psychopathy?against these
in incremental analyses. Although some studies have
evaluated the incremental validity of the APSD and/or CPS
vis-a-vis past or concurrent antisocial behavior (Lynam
1997; Poythress et al. 2006), research has not yet addressed
the incremental validity of the CPS and APSD in juvenile
justice settings in terms of predicting future recidivism.
Data on the PCL:YV are inconsistent, with some studies
reporting incremental validity (Gretton et al. 2004; Schmidt et al. 2006) and others not (Langstrom and Grann
2002). Further, only one of these studies (Schmidt et al.
2006) used a prospective design. Lack of incremental
validity suggests that, for predictive purposes, the measures
may have been related to outcome because they contain
information about these other risk factors (i.e., past crime
and substance related problems both enter into the assess
ment of psychopathy). This study has four primary limitations. First, the sample
size is moderate. Although large samples are always pref
erable to modest ones, in our view the sample size was
justifiable given the research questions. That is, these mea
sures had never been compared to one another in a
prospective study using justice-involved youth. Further, the
APSD and CPS had rarely been used to predict criminal
recidivism within delinquent youth. Hence, given that our
specific research questions had not been addressed previ ously, we reasoned that a moderate sized study7 was
justifiable and appropriate under the circumstances. None
theless, especially for multivariate analyses, we urge caution in interpreting the findings, in that power for such analyses is affected by a host of factors (i.e., base rate; beta; correlation between covariates). This is especially so for analyses of
weapons-related recidivism, given its base rates (7.2%). Second, our sample included both sexual and general
offenders, which in principle could have limited its gen
eralizability if results had differed dramatically between
sub-groups. However, we found that offender type mod
erated just one psychopathy-recidivism relationship. This
suggests that the current findings were not unduly influ enced by sample mix. In fact, sample mix could be viewed as adding to the generalizability of the findings.
Third, to measure recidivism, we relied upon official recidivism data solely. While this is a common method both in psychopathy research and the risk assessment field more broadly, it underestimates the true base rate of recidivism (a well-known phenomenon in criminology
7 We note that with the current sample size, statistical power was
adequate for analyses conducted, with moderate size effects (Cohen
1992) being detected as significant.
referred to as the "dark figure" of crime?see Coleman and
Moynihan 1996). This might have been exacerbated by limiting the source of recidivism data to Florida DJJ
records. Any recidivism that occurred outside of Florida
would not have been detected. As might be the case with
other studies of psychopathic features and recidivism
among adolescents (Corrado et al. 2004; Gretton et al.
2001, 2004; Vincent et al. 2003), the effect of this meth
odological feature would likely be to underestimate the
validity estimates derived for the psychopathy (or any
other) measures. We considered this design feature war
ranted given that our research was the first to compare these three measures in a prospective design. Nonetheless,
we would recommend that more resource-intensive follow
up procedures be employed that include self- and collat
eral-report as sources of recidivism information. We also
note that we were able to derive strong predictive models
from the covariates, suggesting that the method of mea
suring recidivism may not have unduly affected the
predictive validity of measures.
Fourth, there was lower than preferable internal con
sistency for some measures (Nunnally and Bernstein
1994). These values, despite being low, actually are quite consistent with others reported in the literature (for the
APSD, see Cruise et al. 2000; Falkenbach et al. 2003; Lee et al. 2003; Murrie and Cornell 2002; Pardini et al.
2003; Poythress et al. 2006; for the PCL:YV, see Lee et al. 2003; Skeem and Cauffman 2003; Vincent 2002),
suggesting that a feature of the measures, rather than a
deficit of the current study, contributed to the low reli
ability of some of the indices. Given this, low reliability has substantive meaning vis-a-vis validity, which is lim
ited by this feature of the measures. If lower than
preferred reliability is a feature of the measures them selves rather than a feature of the particular study, it is
important to understand the predictive and incremental
validity of the measures as they currently exist, whether
reliability is low or high. In fact, this and other research
(Poythress et al. 2006) can be taken in part as evidence that some of the youth measures of psychopathic features
likely are in need of improved reliability. Further, we note that the base rate of weapons-related
recidivism was small. Hence, results based on this outcome
criterion should be considered with perhaps additional
skepticism, and are in particular need of replication in
independent samples. Finally, we wish to issue a caveat. Given that this was
one of the first comparative studies of these three psy chopathy measures in a prospective research design among
justice-involved youth, we do not consider the issue settled
regarding which measure might have the most utility for
predictive purposes. Although the PCL:YV received very little support in the current study, others have indeed
^ Springer
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436 Law Hum Behav (2008) 32:423-438
observed meaningful associations with criminal conduct in either retrospective follow-up (Gretton et al. 2001, 2004) or prospective designs (Vincent et al. 2003), although the latter with small to moderate effects. Concerning the APSD and CPS, there is simply not yet enough research on pre dictive validity, stemming from prospective studies, within
juvenile justice settings to conclude that our observed
findings reflect a stable, generalizable pattern of predictive effects. For this reason, we strongly encourage other
researchers to attempt to replicate and improve upon our
research using larger sample sizes, more comprehensive
follow-up procedures (i.e., including self-report of recidi
vism) and attending to issues of diversity (i.e., does gender or race moderate the predictive effect of the measures?).
Acknowledgment Kevin S. Douglas gratefully acknowledges the
support of the Michael Smith Foundation for Health Research for
providing him with a Career Scholar Award. Douglas also is affiliated
with Mid-Sweden University, Sundsvall, Sweden, as a Guest Pro
fessor of Applied Criminology.
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