Borderline personality disorder in adolescents: evidence in support of the
Childhood Interview for DSM-IV Borderline Personality Disorder in a
sample of adolescent inpatients
Carla Sharpa,⁎, Carolyn Haa, Jared Michonskia, Amanda Ventaa, Crystal Carboneb
aUniversity of Houston, Houston, TX 77004, USA
bThe Menninger Clinic, Houston, TX 77080, USA
Empirical evidence is increasing in support of the validity of the construct of borderline personality disorder (BPD) in adolescence.
There is growing consensus that the early identification and treatment of emerging borderline traits may be an important focus. However,
few diagnostic (questionnaire- or interview-based) measures specifically developed or adapted for adolescents and children exist. The
Childhood Interview for DSM-IV Borderline Personality Disorder (CI-BPD) [Zanarini, 2003] is a promising interview-based measure of
adolescent BPD. Currently, no studies have explicitly been designed to examine the psychometric properties of the CI-BPD. The aim of the
current study was to examine various psychometric properties of the CI-BPD in an inpatient sample of adolescents (n = 245). A
confirmatory factor analytic approach was used to examine the internal factor structure of the 9 CI-BPD items. In addition, internal
consistency, interrater reliability, convergent validity (with clinician diagnosis and 2 questionnaire-based measures of BPD), and concurrent
validity (with Axis I psychopathology and deliberate self-harm) were examined. Similar to several adult studies, the confirmatory factor
analytic results supported a unidimensional factor structure for the CI-BPD, indicating that the Diagnostic and Statistical Manual of Mental
Disorders, Fourth Edition, criteria on which the CI-BPD is based constitute a coherent combination of traits and symptoms even in
adolescents. In addition, other validity criteria were excellent. Taken together, the current study provides strong evidence for the validity of
the CI-BPD for use in adolescents.
© 2012 Elsevier Inc. All rights reserved.
Borderline personality disorder (BPD) is a serious
disorder that has been linked to high rates of suicide
completion in adults, ranging from 4% to 10% . BPD
represents a significant burden to society in terms of distress
and burden placed on medical and mental health communi-
ties, as well as families [2-4]. Despite the fact that BPD
typically emerges in adolescence , it was not until the
Diagnostic and Statistical Manual of Mental Disorders,
Fourth Edition (DSM-IV)  that the diagnosis of BPD in
youth was permitted. The same diagnostic criteria used in
diagnosing adult BPD were retained in making this
extension, but the duration of symptom presentation was
reduced from 2 years to 1, with the qualification that the
characteristic personality traits were expected to be perva-
sive, persistent, and not limited to the developmental period
of adolescence or to an episode of an Axis I disorder.
Despite this allowance, diagnosing youth with BPD has
engendered a great deal of reluctance for several reasons.
First, the diagnosis of personality disorders in adolescents is
associated with controversy [2,7,8] because of the perception
that personality is unstable in adolescence , the stigma
associated with a diagnosis of personality disorder, and the
suggestion that symptoms of BPD are better explained by
Axis I symptoms . However, there has been a steady
increase in evidence supporting the diagnosis of juvenile
BPD [11-13], including evidence for longitudinal continuity
[14-16], a genetic basis [17-19], overlap in the latent
variables underlying symptoms [20-22] and the risk factors
[23-25] for adolescent BPD and the full-blown adult
disorder, and evidence for marked separation of course and
outcome of adolescent BPD and other Axis I and Axis II
disorders [10,14,26,27]. As in adults, children and
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Comprehensive Psychiatry 53 (2012) 765–774
E-mail address: firstname.lastname@example.org (C. Sharp).
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adolescents diagnosed with the disorder have increased rates
of hospitalization because of suicidal ideation or attempts
; more severe Axis I pathology , as also shown by
the work of Chanen et al ; and poorer clinical and
psychosocial functioning compared with other personality
disorders . Together, the work of Chanen et al and the
Child in the Community Study have pointed to the
importance of early intervention and prevention of the
disorder in youth [10,30] because research has suggested
the malleability of BPD symptoms in adolescence .
Early intervention is, however, hampered by a general
lack of valid and reliable measures to identify adolescents
with BPD traits. Currently, there is only 1 published
interview-based measure specifically adapted for use in
children and adolescents. The Childhood Interview for
DSM-IV Borderline Personality Disorder (CI-BPD)  was
developed specifically for use with youth, but published
studies examining its psychometric properties are lacking.
Three published studies that we are aware of have used it, but
none of them have explicitly investigated the psychometric
properties of the CI-BPD. Zanarini et al  used it in a
sample of 6410 11-year-old children in the United Kingdom.
Children were interviewed in person by a trained rater. This
yielded 6330 (98.8%) interviews with complete data. Of
those with complete data, 3273 (51.7%) were girls and 3057
(48.3%) were boys. Interrater reliability using taped in-
terviews of 30 children revealed κ values ranging from 0.36
to 1.0, with a median value of 0.88. Overall, 86% of the κ
values were in the excellent range of greater than 0.75. The
CI-BPD was used in 2 additional studies, both showing
significant κ's with clinician ratings of BPD diagnosis
[34,35]. Together, these studies are promising for the
criterion validity of the CI-BPD, but as yet, no information
exists on the internal factor structure of the CI-BPD, its
concurrent and convergent validity, and interrater reliability
in a study explicitly designed to examine the psychometric
properties of the CI-BPD.
To this end, our study aimed to investigate the
psychometric properties of the CI-BPD in a sample of
adolescent inpatients ages 12 to 17 years. We used latent trait
analyses to examine the measure's internal factor structure,
expecting a unidimensional factor structure based on 6
studies supporting a unidimensional factor structure in adult
patients [36-40], adult community samples , and a small
adolescent sample of 60 French high school students .
Convergent validity was examined through the inclusion of 2
questionnaire-based measures of BPD especially designed
for children and adolescents: the Borderline Personality
Disorder Feature Scale for Children  and the Personality
Assessment Inventory for Adolescents , in addition to
clinician diagnosis. Concurrent validity was determined by
examining relations with Axis I psychopathology, which
included both parent-report and self-report questionnaire–
based measures as well as an interview-based diagnostic
measure. We expected that patients identified as borderline
by the CI-BPD would have higher prevalence of both
internalizing and externalizing problems as found by
previous studies of adolescent BPD [44,45]. Concurrent
validity was further determined by examining whether those
identified as borderline on the CI-BPD had significantly
higher frequencies of self-harm, suicidal behavior as
suggested in adult  and adolescent studies , as well
as higher levels of emotion dysregulation, as suggested by
work in adults .
Against the background of a growing trend to view
psychiatric disorders, especially personality, from a dimen-
sional perspective rather than categorically [49–53], we
examined the performance of the CI-BPD both categorically
(5 of more criteria met) and dimensionally (0-2 scale scores
on 9 CI-BPD items). A dimensional perspective may be
particularly important for conceptualizing BPD pathology
among youth because it is better able to account for
developmental fluctuations and increased heterogeneity,
which have been reported in younger samples .
Consecutive admissions (n = 245) to an adolescent unit at
an inpatient psychiatric clinic were administered a battery of
self-report and interview-based assessments during the first 2
weeks of their stay. Parent reports were also obtained on this
sample of 12- to 17-year olds. The average stay in the
hospital was 4 to 6 weeks. In total, 44 subjects were excluded
from the final analyses for various reasons. Following
institutional review board protocol and ethical consider-
ations, adolescents were not forced to complete all
assessments and were not required to explain why they
opted out of any individual assessment. On this basis, 20
patients declined participation in research. In addition, 9
were not consented because of language barrier or having an
IQ of less than 70. Other exclusions included families who
revoked consent (n = 2), psychotic disorder (n = 6), and early
discharges before completion of the assessments (n = 7).
After exclusions, 201 participants remained, of which an
additional 11 were excluded from the final analyses because
of missing CI-BPD data.
The final sample size was therefore n = 190, with a mean
age of 15.39 years (SD = 1.45), of which 113 were females
and 77 were male, and the sample was predominantly middle
to upper-middle class, with 91.6% whites (n = 174) and 7.9%
nonwhites (n = 15).
3.1. Borderline personality disorder
3.1.1. Childhood Interview for DSM-IV Borderline
The CI-BPD  is a semistructured interview developed
specifically for use with children and adolescents to assess
766C. Sharp et al. / Comprehensive Psychiatry 53 (2012) 765–774
BPD. The interview was adapted from an adult assessment of
DSM-IV personality disorders, with items modified from the
borderline module of the Diagnostic Interview for Person-
ality Disorders . The youth version was adapted by
Zanarini  for youth in the following ways: (1) the
language was simplified, (2) 2 forms of impulsivity (ie,
promiscuity and reckless driving) were omitted because it
was thought that they would not be applicable to children,
and (3) the interview was made more structured than its adult
counterpart. A total of 9 criteria reflecting symptoms of BPD
are rated using “0” for symptoms that are absent, “1” if the
symptom is probably present, or “2” for symptoms that are
definitely present. A minimum of 5 criteria scored “2” are
required for a full diagnosis of BPD. Similar to the adult
criteria for a DSM-IV diagnosis of BPD, the 9 criteria on the
CI-BPD interview assess for clinical symptoms of inappro-
priate and intense anger, affective instability, chronic
feelings of emptiness, identity disturbance, transient stress-
related paranoid ideation or severe dissociative symptoms,
fears of abandonment, recurrent suicidal behavior, gestures
or threats or self-mutilating behavior, impulsivity, and a
pattern of unstable and intense interpersonal relationships. A
dichotomous score on the CI-BPD was used in the analyses
to establish reliability and validity, with nondiagnosis scored
“0” and full diagnosis of BPD scored “1.”
Training on the CI-BPD involved several stages, which
occurred in the following order: (1) didactic training by the
first author (who was trained by the developers of the CI-
BPD), (2) shadowing of interviews, (3) a practice interview
with nonpatient, (4) interview with experienced interviewer
critiquing, and finally, (5) independent interviews. All
interviews were video recorded. Monthly consensus meet-
ings were held as booster sessions where video recordings
were reviewed as a group to assure fidelity to the interview-
3.1.2. Clinician diagnosis of BPD
Clinician diagnosis of BPD at discharge was used in this
study. Discharge diagnosis was used because clinicians defer
Axis II diagnosis at admission to obtain more information
over time while adolescents are inpatients. Chart diagnoses
were informed by input from multidisciplinary team
members over the course of the adolescent stay. Full
diagnosis of BPD was coded as “1,” and no diagnosis or
emerging traits were coded with a “0.”
3.1.3. Personality Assessment Inventory for Adolescents
The Personality Assessment Inventory for Adolescents
(PAI-A)  is a 264-item self-report measure of personality
functioning that was adapted from the adult version of the
Personality Assessment Inventory (PAI) with the goal of
retaining the basic structure of the original test. A normative
sample of 707 adolescents from ages 12 to 18 years was used
in standardization, and stratification was used according to
demographic variables including age, sex, and ethnicity.
Items are worded for a fourth-grade reading level, and
adolescents are instructed to rate how true they think each
statement is for them based on 4 response options ranging
from “false,” “slightly true,” “mainly true,” and “very true.”
Adequate psychometric properties have been demonstrated
for the PAI-A , and comparable inter-item correlations
with the adult version have been established. Similar to the
adult version, the PAI-A has 22 nonoverlapping scales that
are organized into 4 validity scales, 11 clinical scales, 5
treatment consideration scales, and 2 interpersonal scales.
The PAI-A scale raw scores are converted to T scores that
have a mean of 50 and SD of 10. We used the T score of the
borderline scale (PAI-A BOR) and its relevant subscales
(affective instability, BOR-A; identity problems, BOR-I;
negative relationships, BOR-N; and self-harm, BOR-S).
Research on the PAI BOR scales in the adult version has
established adequate validity for all BOR scales . To
assess for suicidal ideation, we also use the T score on the
PAI-A suicide (PAI-A SUI) scale.
3.1.4. Borderline Personality Features Scale for Children
The Borderline Personality Features Scale for Children
(BPFSC) is a self-report measure developed to assess
borderline personality features in children as young as 9
years old . The measure was adapted from the borderline
scale of the PAI  to assess affective instability, identity
problems, negative relationships, and self-harm. Adolescents
are asked to rate how they feel about themselves and others
using a 5-point Likert scale with responses ranging from 1
“not at all true” to 5 “always true.” A parent-report version
(BPFSP)  has been developed from the self-report
measure with the original items slightly modified from first
person to third person point of view (eg “I feel very lonely”
was replaced with “My child seems to feel very lonely”).
Adequate psychometric properties have been demonstrated
for both parent- and self-reported measures with concordant
and concurrent validity established in a community sample
, and criterion validity demonstrated in an inpatient
sample of adolescents . In the current study, dimensional
scores were used for both parent- and self-reported
borderline features. High scores indicate high levels of
BPD symptoms, and low scores reflect low symptoms.
3.2. Axis I psychopathology
3.2.1. Youth Self-Report and Child Behavior Checklist
Parents and adolescents completed ratings of Axis I
psychopathology. The Youth Self-Report (YSR) has 112
problem items, whereas the Child Behavior Checklist
(CBCL) has 113 . Both are well established self- and
parent-report measures of psychopathology. Criterion and
construct validity have been demonstrated for both parent
and youth reports . Both measures are scored using a 3-
point scale with “0” for not true, “1” for somewhat or
sometimes true, or “2” for very or often true. Eight syndrome
scales make up the 2 broader scales for internalizing and
externalizing problems in both adolescent and parent report
forms. Anxious/depressed, withdrawn/depressed, and
767C. Sharp et al. / Comprehensive Psychiatry 53 (2012) 765–774
somatic complaints subscales comprise the internalizing
problem scale, and rule-breaking and aggressive behavior
subscales are summed for the externalizing problem scale. A
total problems scale is derived by summing all subscales
including anxious/depressed, withdrawn/depressed, somatic
complaints, social, thought, attention problems, aggressive
and rule-breaking behaviors. For analyses, we used T scores
for the internalizing, externalizing, and total problems scales.
3.2.2. Diagnostic Interview Schedule for
The Diagnostic Interview Schedule for Children—
Computerized Version (DISC-IV)  is a structured
clinical interview used to assess for Axis I psychopathology
in children and adolescents ages 9 to 17 years. The
computerized version was used for this research, requiring
the interviewer to read each question out loud from a
computer screen and select a response based on the answer
that the adolescent provides. The interviews were adminis-
tered individually by trained staff in a private assessment
room, and the length of interviews ranged from 1 1/2 to 2
hours.Positive diagnoses onthe clinicalreportsof the DISC-IV
were coded as “1,” whereas both intermediate and negative
diagnoses were coded as “0” for the analyses. Dichotomous
summary scores were created for “any anxiety disorder” if
(social phobia, specific phobia, panic disorder, agoraphobia,
generalized anxiety disorder, posttraumatic stress, and obses-
sive-compulsive disorders). A similar strategy was used for
other diagnostic categories. A patient met criteria for “any
depressive disorder” if s/he met criteria on either of the
modules of dysthymia or major depressive disorder. A patient
met criteria for “any bipolar disorder” if s/he met criteria on
either of the modules of mania and hypomania. Finally, the
anorexia and bulimia modules were coded as “any eating
disorder,” and modules for conduct disorder, oppositional
defiant disorder, and attention-deficit/hyperactivity disorder
were grouped into “any externalizing disorder.”
3.3. Deliberate Self-Harm
The Deliberate Self-Harm Inventory (DSHI)  is a self-
report measure containing 17 items assessing for the
presence and frequency of various self-harm behaviors.
Adequate psychometric properties have been reported with
high internal consistency and good test-retest reliability .
In this study, we use the continuous total score on the DSHI.
High scores reflect a high frequency of self-harm, and low
scores indicate low frequency.
3.4. Emotion regulation
3.4.1. Difficulties in Emotion Regulation Scale
The Difficulties in Emotion Regulation Scale (DERS)
 is a 36-item self-report assessment of emotion
dysregulation. Adolescents are asked to rate the frequency
of each statement using a Likert-type scale ranging from 1
(almost never) to 5 (almost always). A total score of emotion
dysregulation is derived by summing all responses, with
additional emotion regulation domains assessed for includ-
ing (1) awareness and understanding of emotions, (2)
acceptance of emotions, (3) the ability to engage in goal-
directed behavior and refrain from impulsive behavior when
experiencing negative emotions, (4) access to emotion
regulation strategies perceived as effective, and (5) the
flexible use of situationally appropriate strategies to
modulate emotional responses . For the purposes of
this study, we used the total emotion dysregulation score,
with higher scores indicating greater emotion regulation
difficulties. Adequate psychometric properties of the mea-
sure and good internal consistency (α = .86) have been
The Wechsler Scales [61,62]: Wechsler Intelligence Scale
for Children—Fourth Edition (WISC-IV) and Wechsler
Adult Intelligence Scale—Fourth Edition (WAIS-IV), were
used to assess for IQ in patients. These assessments are well-
established, standardized measures for assessing IQ with
good psychometric properties . Clinicians administered
this assessment to all adolescents unless it was determined
that the patient was ineligible for testing because of active
psychosis. Older patients 16 to 17 years old typically
received the WAIS-IV, whereas younger patients (16 and
younger) received the WISC-IV. For this study, we used the
Full Scale IQ composite score.
The study was approved by the local institutional review
board. Parents and adolescents completed all self-report
measures through a secure Web-based system developed by
the inpatient facility. A trained research assistant remained in
the assessment room to answer questions. Diagnostic
interviews were administered individually and in private
with patients by licensed clinicians, doctoral-level clinical
psychology students, and trained clinical research staff,
under the direct supervision of the principal investigator
(first author). All assessments were completed by parents
and adolescents within the first 2 weeks after admission.
3.7. Data analytic strategy
The factor structure of the 9 BPD criteria was examined
using confirmatory factor analysis (CFA), performed using
Mplus version 6.0 software Mplus, Los Angeles, CA .
Given the ordered categorical response format of the CI-
BPD, a robust weighted least squares estimation procedure
(WLSMV) was used. WLSMV has been found to perform
well for 2 and 3 response categories [65,66]. Confirmatory
factor analysis models with categorical indicators generally
require large sample sizes to obtain accurate test statistics,
parameter estimates, and standard errors . However, for
simple models with a modest number of indicators (as in the
present investigation), sample sizes of 150 to 200 have been
768C. Sharp et al. / Comprehensive Psychiatry 53 (2012) 765–774
found to be sufficient [66,67]. Following conventions,
goodness of fit for the CFA models was evaluated using a
variety of fit statistics. The χ2goodness-of-fit statistic
provides an index of absolute model fit. A nonsignificant χ2
value (P ≥ .05) indicates that the model adequately
reproduces the observed covariance matrix. Other commonly
reported indices of model fit include the root mean square
error of approximation (RMSEA) , Bentler CFI , and
the Tucker-Lewis index (TLI) . For RMSEA, values less
than 0.05 indicate good fit and values between 0.05 and 0.08
indicate adequate fit [67,71]. For CFI and TLI, values close
to 0.95 or greater suggest good model fit [67,72].
To investigate the CI-BPD's reliability and validity, we
ran descriptive analyses to determine means, SDs, and
ranges (Table 1). Next, χ2tests and independent-samples t
tests were conducted to investigate the relation between CI-
BPD diagnosis with other measures of BPD (PAI-A and
BPFS scores), and with Axis I psychopathology, suicidal
ideation, self-harm behaviors, and emotion dysregulation.
BPD diagnoses were also examined in relation to demo-
graphic variables including sex and age. Next, a correlational
analysis was conducted to examine continuous scores on
BPD with Axis I pathology, suicidal ideation, self-harm
behaviors, and emotion dysregulation to further verify the
CI-BPD's concurrent and convergent validity (Table 2).
Kappa analyses were conducted to examine the agree-
ment between CI-BPD and clinician diagnoses of BPD as
well as interrater reliability on the CI-BPD. Internal
reliability was determined through Cronbach α. These
analyses were carried out using SPSS version 18 (SPSS,
4.1. Preliminary analyses
Descriptive statistics are reported for main study variables
in Table 1. Of the final sample (n = 190), 26% (n = 49) of
adolescents met criteria for a diagnosis of BPD. The PAI-A
was added to the assessment battery at a later time point, so
subjects were grouped into pre- and post-PAI scores to
examine systematic differences between those who received
PAIs and those who did not. Chi-square analyses revealed no
significant differences in CI-BPD scores between those who
completed the PAI and those who did not (χ21= 0.02, P =
.87). The CBCL, YSR, and DSHI were incomplete for a few
cases and were excluded from the analyses. As expected, our
sample was composed of significantly more females (83.7%)
who met criteria for BPD than males (χ21= 16.04, P b .001).
4.2. Confirmatory factor analysis
Confirmatory factor analysis results revealed that a 1-
factor model showed adequate fit: χ227= 55.22, P b .001;
RMSEA = 0.07; CFI = 0.96; TLI = 0.94. Further support of a
unidimensional factor structure is evidenced by the magni-
tude of the first eigenvalue (4.58) extracted from the
Descriptive statistics for main study variables
Study variablen Mean (SD)Minimum Maximum
PAI-A suicidal ideation
PAI-A subscales: affective instability (PAI-A BOR-A), identity problems
(PAI-A BOR-I), negative relationships (PAI-A BOR-N), and self-harm
Pearson correlations between CI-BPD continuous scores with emotion regulation and psychopathology measures
CI-BPD YSR internalYSR external CBCL internalCBCL external DERS PAI-A BORBPFSC BPFSP DSHI
If Bonferroni correction is applied, P = .005, which means all variables still remain significantly correlated with the CI-BPD continuous score.
⁎P b .05.
⁎⁎P b .001.
769C. Sharp et al. / Comprehensive Psychiatry 53 (2012) 765–774
polychoric correlation matrix relative to subsequent eigen-
values (1.08 and 0.93 for the second and third eigenvalues,
respectively). Standardized factor loadings ranged from 0.60
to 0.79: unstable relationships (0.79), identity disturbance
(0.75), abandonment fears (0.74), affective instability (0.74),
suicidal behaviors (0.67), uncontrolled anger (0.62), chronic
emptiness (0.61), transient paranoid ideation (0.60), and
4.3. Internal reliability
Internal consistency was good with a Cronbach alpha of
.80 for the 9 items on the CI-BPD.
4.4 Interrater reliability
Interrater reliability was performed on 15% of the sample
(n = 31), with 2 independent raters trained by the principal
investigator of the study. The results of the interrater
analyses showed a κ = 0.89.
4.5. Convergent validity
Clinician diagnoses were significantly related to CI-BPD
diagnoses (κ = .34, P b .001). Independent-samples t test
with CI-BPD dichotomous scores as the independent
variable and scores on the BPFSP, BPFSC, PAI-A BOR,
and subscales as dependent variables confirmed that CI-BPD
diagnoses were significantly associated with other measures
of BPD as reported by patients and parents. Means and
standard deviations are reported in Table 3. Patients who met
criteria for BPD as assessed by the CI-BPD had significantly
higher means on both the BPFSP (t171= −2.59, P = .01) and
BPFSC (t183 = −6.86, P b .001), when compared with
patients who did not meet criteria for BPD. As expected, CI-
BPD diagnoses revealed significantly higher means on the
PAI-A Borderline Features scale (t165= −7.15, P b .001),
including all PAI-A Borderline subscales: affective instabil-
ity (t165= −6.79, P b .001), identity problems (t165= −5.13,
P b .001), negative relationships (t165= −5.32, P b .001),
and self-harm (t165= −5.37, P b .001).
To examine the above relations dimensionally, continu-
ous scores on the CI-BPD were correlated with scores on the
BPFSP, BPFSC, and PAI-A BOR.Results from correlational
analyses revealed significant relationships between the CI-
BPD and the other measures of BPD (Table 2). These
findings support both the convergent and criterion validity of
using the CI-BPD in an adolescent inpatient setting.
4.6. Concurrent validity
Next, we assessed concurrent validity by conducting
independent-samples t test with CI-BPD diagnoses and Axis
I psychopathology, suicidality, self-harm, and emotion
dysregulation. Means and standard deviations for borderline
and nonborderline patients are reported in Table 3. As
expected, adolescents with a BPD diagnosis indicated by the
CI-BPD had significantly higher severity in Axis I pathology,
scoring higher in CBCL internalizing (t181= −2.28, P = .02),
CBCL externalizing (t181= −3.00, P = .003), and CBCL total
problems (t181= −3.20, P = .002). The same was found for
self-reported Axis I problems on the YSR with internalizing
(t186= −3,59, P b .001),externalizing(t186= −5.88,P b .001),
and total problems (t186= −6.20, P b .001). Patients who
received a diagnosis of BPD also had higher means in suicidal
ideation (t165= −4.78, P b .001) and in deliberate self-harm
(t183= −4.74, P b .001) than non-BPD's. Analyses with CI-
BPD scores and emotion regulation confirmed that BPD
patients had significantly higher scores on difficulties in
emotion regulation (t188= −6.13, P b .001) compared with
non-BPDs. Concurrent validity was also assessed using
continuous scores from the CI-BPD with Axis I psychopa-
thology, suicidality, emotion regulation, and self-harm.
Correlations revealed significant relations in the expected
directions for all measures (Table 2).
Furthermore, χ2analyses revealed that patients with a CI-
BPD diagnosis were significantly overrepresented for Axis I
psychopathology as measured by interview-based diagnosis
Convergent and concurrent validity (means and SDs)
BPD No BPD
n Mean SDn Mean SD
PAI-A suicidal ideation
Percentage of BPD vs non-BPD patients receiving a comorbid diagnosis of
any Axis I psychopathology
CDISC diagnosesCIBPD diagnosesχ2analysis
BPD (n = 49)Non-BPD (n = 141)
Any eating disorder
If Bonferronicorrections for multiple comparisons are applied, alpha is set at
.008, which means that all variables except “any anxiety” and “any eating
disorder” remain significant.
770C. Sharp et al. / Comprehensive Psychiatry 53 (2012) 765–774
(Table 4). Those with BPD were significantly more likely to
have a diagnoses of any anxiety (χ21= 6.43, P = .01), mood
(χ21= 12.81, P b .001), depressive (χ21= 8.66, P = .003),
eating (χ21= 5.81; P = .02), and externalizing disorders
(χ21 = 11.16, P = .001). Patients with BPD were also
overrepresented for bipolar disorders (χ21=7.48, P = .006).
To our knowledge, this is the only (and largest) inpatient
study examining the psychometric properties of a promising
diagnostic instrument for BPD in adolescents. Taken
together, our findings support the validity and reliability of
this instrument. First, the CFA supported a unidimentional
factor structure for the CI-BPD, indicating that the DSM-IV
criteria, on which the CI-BPD is based, constitute a coherent
combination of traits and symptoms even in adolescents.
This result is consistent with the adult BPD literature in
which a unidimensional factor structure has been the
predominant and most parsimonious finding [37-41,73,74].
Although a few studies of adult BPD have favored a
multidimensional factor structure (Refs [73,75-77], most of
these have been conducted with Diagnostic and Statistical
Manual of Mental Disorders, Third Edition or Revised
Third Edition [ie, 8 vs 9 criteria]). Only Sanislow et al 
used the DSM-IV, and their results also supported a single-
factor solution, which was arguably the better model in that
it was more parsimonious (ie, the 3-factor model had high
factor correlations, with r's exceeding 0.90). The 3-factor
model also had conceptual problems (eg, abandonment
fears loaded on the “affective dysregulation” factor along
with affective instability and uncontrolled anger, rather
than the “disturbed relatedness” factor). Thus, it is now the
case that a single-factor solution is favored in more studies
than a multidimensional factor structure. Notably, this
includes studies treating the criteria as ordinal rather than
continuous variables and using more robust estimation
The CFA further revealed that factor loadings of the
magnitude reported are comparable with those reported in
the adult literature [37,38,41,73], lending further support for
the validity of this instrument. In addition, the percentage of
adolescent inpatients identified by the CI-BPD as meeting
criteria for BPD reflects findings by other studies in
adolescent inpatient settings, which have reported from
33%  to as high as 48% to 53% of their sample receiving
the BPD diagnosis [79,80].
Third, internal consistency was found to be good, and
interrater reliability was excellent. The fact that nonclinicial
raters can be trained to use the CI-BPD with high interrater
reliability speaks to the practical application of this measure
in research settings. Convergent validity was indicated with
significant agreement between the CI-BPD and clinician
diagnosis. Moreover, patients diagnosed with BPD on the
CI-BPD had significantly higher scores on all 3 question-
naire-based measures of BPD, providing additional support
for convergent validity. Finally, concurrent validity was
demonstrated by higher frequencies of deliberate self-harm,
Axis I psychopathology (both questionnaire-based and
interview-based), higher levels of emotion dysregulation,
and suicidality in the BPD vs the non-BPD groups.
The above findings were also evident for when
continuous scale scores of the CI-BPD were used. Although
clinicians are unlikely to use continuous scores within the
current diagnostic practice, there is now good evidence that a
dimensional perspective may add richness to the diagnostic
process [49-53]. As mentioned in the introduction, a
dimensional perspective may be particularly important for
conceptualizing BPD pathology among youth because it is
better able to account for developmental fluctuations and
increased heterogeneity that have been reported in younger
samples . Indeed, the proposed changes for the DSM-V
incorporate a dimensional approach for classification and
diagnosis of personality disorders. The CI-BPD can be easily
adapted for DSM-V use in that all 9 criteria are retained in the
DSM-V proposal: criterion A includes identity disturbance,
emptiness, dissociation, and unstable relationships, whereas
criterion B includes affective instability, abandonment fears
(separation insecurity), suicidal behavior (under the depres-
sivity criterion), impulsivity, and anger. The CI-BPD can be
expanded to include empathy, self-direction, and anxious-
ness, which are not currently covered in the DSM-IV –based
CI-BPD, and used as a dimensional measure.
Despite these promising findings, some limitations to the
study should be acknowledged. First, our sample was
composed mostly of middle to upper middle-class social
class and predominantly of white adolescents. Therefore, it is
unknown whether the CI-BPD is a reliable and valid
assessment tool for use in other populations such as those
with low socioeconomic status and with a more diverse
ethnic background. Our study does not address test-retest
reliability of the CI-BPD in diagnosis of inpatient adoles-
cents. Furthermore, our participants represented adolescent
patients at the severe end of the psychopathology spectrum
who failed to respond to previous treatments, so these results
may not generalize to adolescent outpatients. It is therefore
important to also validate the CI-BPD in nonclinical
populations or less severe populations. Finally, BPD is a
complex construct, and the heterogeneity of the disorder
complicates diagnostic classification. Many researchers have
argued that BPD in adolescence is an aspect of Axis I
pathology [81,82], yet others have demonstrated that despite
association with Axis I disorders, BPD is reliably and
validly diagnosed in this age group [54,78,83]. Given that
our study aim was to validate the CI-BPD instrument, we
cannot directly address the issue of whether BPD is not
simply a form of Axis I pathology. Future studies should
examine the discriminant validity of BPD in relation to Axis
I disorders in adolescence.
In conclusion, the diagnosis of personality disorders in
adolescents is still associated with controversy [2,7,8], and
771 C. Sharp et al. / Comprehensive Psychiatry 53 (2012) 765–774
some clinicians continue to appear to be reluctant to consider
a diagnosis of personality disorder even in adults . It is
therefore imperative that more research is carried out to
examine the course, etiology, and phenomenology of
adolescent BPD. Doing so requires valid and reliable
measures of adolescent BPD. Against this background, the
current study is important in that itprovides good evidence in
support of the validity and the reliability of a relatively new
instrument for the interview-based assessment of BPD in
youth. In this sense, by demonstrating adequate psychomet-
rics for an interview-based measure of juvenile BPD, the
current study contributes to the growing body of evidence in
support of the juvenile BPD construct, including evidence
for longitudinal continuity [14,15], marked separation of
course and outcome of adolescent BPD and other Axis-I and
Axis-II disorders [14,26,27], and a genetic basis for
adolescent BPD [17-19]. In addition, overlap between
adult BPD in the latent variables underlying symptoms
[20-22] and the risk factors [23-25,35] associated with
adolescent BPD have been demonstrated. These studies can
be built on with strong measures such as the CI-BPD.
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