•For this assignment, select a construct you may want to use in your future dissertation (e.g. aggression, burnout, social anxiety, emotional intelligence).
•Find two different measurements that measure this construct. Include an overview of each measurement- what do they measure and how (scale information).
•How are the tests similar/different? What may be the advantages of using one test over another?
•Report reliability (numbers) for each scale based on research (provide citations)
•Length: 1-2 pages
•Include APA style cover page, headings, citations & references
An Icelandic version of the
cross-cultural adaptation and
´ BERTRAND LAUTH, PA ´ LL MAGNU ´ SSON, PIERRE FERRARI, HANNES PETURSSON
Lauth B, Magnússon P, Ferrari P, Pétursson H. An Icelandic version of the Kiddie-SADS-PL:
Translation, cross-cultural adaptation and inter-rater reliability. Nord J Psychiatry 2008;62:
379�385. Oslo. ISSN 0803-9488.
The development of structured diagnostic instruments has been an important step for research
in child and adolescent psychiatry, but the adequacy of a diagnostic instrument in a given culture
does not guarantee its reliability or validity in another population. The objective of the study
was to describe the process of cross-cultural adaptation into Icelandic of the Schedule for
Affective Disorders and Schizophrenia for School-Age Children*Present and Lifetime Version
(Kiddie-SADS-PL) and to test the inter-rater reliability of the adapted version. To attain cross-
cultural equivalency, five important dimensions were addressed: semantic, technical, content,
criterion and conceptual. The adapted Icelandic version was introduced into an inpatient clinical
setting, and inter-rater reliability was estimated both at the symptom and diagnoses level, for the
most frequent diagnostic categories in both international diagnostic classification systems
(DSM-IV and ICD-10). The cross-cultural adaptation has provided an Icelandic version
allowing similar understanding among different raters and has achieved acceptable cross-
cultural equivalence. This initial study confirmed the quality of the translation and adaptation of
Kiddie-SADS-PL and constitutes the first step of a larger validation study of the Icelandic
version of the instru
� Child psychiatric interview, Diagnostic instruments, Inter-rater reliability, K-SADS-PL,
Translation and cross-cultural adaptation.
Bertrand Lauth, University of Iceland, Landspitali University Hospital, Department of Child
and Adolescent Psychiatry, Dalbraut 12, 105 Reykjavı́k, Iceland, E-mail: bertrand@landspitali.
is; Accepted 20 September 2007.
he development of structured diagnostic instruments
has been an important step for research in child and
adolescent psychiatry. These standardized instruments
are based on the more descriptive taxonomy of recent
editions of international classification systems, DSM-IV
(1) and ICD-10 (2). They are essential for research and
are good aids for clinicians, since they provide a
structured and systematic assessment procedure that
has increased diagnostic reliability.
However, for researchers belonging to cultural back-
grounds and speaking languages other than English, the
adoption of such an instrument involves a process of
translation and adaptation of the instrument. The
adequacy of the diagnostic instrument in a given culture
does not guarantee its reliability or validity in another
population (3). The challenge for these researchers is then
to develop a translated and adapted version of the
assessment tool, which is equivalent to the original
version of the instrument. Only by achieving this equiva-
lence will it be possible to assure the degree of compar-
ability in studies carried out in different cultures (3).
The need for diagnostic instruments has led the
authors to start the development of a local version of
the Kiddie-SADS-PL for research in clinical populations.
Because of the lack of European consensus statement
about standard and validated practices on that topic, we
started with a classic translation/back-translation process
to try to achieve semantic equivalence and then started to
introduce the structured interview into an adolescent
inpatient clinical setting.
The impact of the introduction of the diagnostic
instrument is described in another publication, as well
as additional studies on the psychometric properties of
the Icelandic version in an adolescent clinical population.
# 2008 Informa UK Ltd. (Informa Healthcare, Taylor & Francis As) DOI: 10.1080/08039480801984214
B LAUTH ET AL.
This article describes the process of translation and
adaptation of the instrument as well as inter-rater
The importance of structured psychiatric interviews
in child and adolescent psychiatry
Research does not support unstructured interviews as
reliable means to standardized diagnoses (4). Even
experienced clinical interviewers are not reliable diag-
nosticians when compared which each other or when
compared with structured interviews (5�8). Agreement is
usually low in studies involving outpatients or hospita-
lized children and adolescents (5, 6, 9�12). Agreement is
usually higher for externalizing disorders than for inter-
nalizing and many authors suggest that diagnoses of
anxiety and depression are often missed using an
unstructured interview. Miller (7, 8) has suggested that
because the structured interview yields precise diagnostic
data, appropriate treatments may be delivered earlier,
leading to more rapid recovery and shorter hospital stays.
Research is still needed to establish the utility of
diagnostic interviews in clinical settings, but by encoura-
ging clinicians to follow standard diagnostic and inter-
viewing methods, they promote more consistent
diagnostic practices and help justify therapeutic inter-
ventions and outcomes. However, the instruments are
not a substitute for clinical judgement. As McClellan &
Werry (13) pointed out, psychiatric decision making
depends on the integration of information from diverse
sources and perspectives, including the patient and
family interviews, the mental status examination, collat-
eral informants (teachers) and other treatment providers.
The pre-eminent role of the clinician must be recognized
Choice of a ‘‘state of the art’’ psychiatric diagnostic
In this project, an interviewer-based diagnostic interview
that requires some clinical decision making on the part
of the interviewer was chosen. This kind of instrument is
often used in studies of clinical populations and is
preferred by clinicians to respondent-based interviews
(13), even though it usually shows poorer reliability.
The ‘‘Kiddie-Schedule for Affective Disorders and
Schizophrenia for School-Age Children’’ (‘‘K-SADS’’)
has changed since its original publication (14) and is
currently available in different DSM-IV format versions:
the Kiddie-SADS-P IVR (Present State), the Kiddie-
SADS-L (Lifetime), the Kiddie-SADS-PL (Present and
Lifetime Version) and the Kiddie-SADS-E (Epidemio-
logical) (15, 16).
The ‘‘Present and Lifetime’’ version (K-SADS-PL)
has several strengths (16). It has strong content validity
because it was designed to tap pre-specified diagnostic
criteria. It has been designed to lead the clinician or the
therapist to make DSM-IV diagnoses during interviews
of the young patient and his parent, including detailed
probes useful in eliciting clinically meaningful informa-
tion. One strength of the Kiddie-SADS-PL is its high
degree of precision and detail in assessing child symp-
toms and their onset, severity, duration and associated
impairments. It is the only instrument that provides
global and diagnosis-specific impairment ratings to
facilitate the determination of ‘‘caseness’’ (17). The
Kiddie-SADS-PL provides also a clinician-friendly front
and screening examination, which may result in a more
efficient shorter interview. Skip-decisions seem reliable
and have been validated by comparison with other
symptom measures (18).
In comparison to other child diagnostic instruments,
the K-SADS-PL compares favourably with test�retest
reliability estimates (17) and adequate concurrent valid-
ity of the K-SADS-PL diagnoses was established against
several standard self-report scales (18). Its strength
remains in diagnoses of affective and anxiety disorders;
it has also been demonstrated to have good reliability for
Use of the Kiddie-SADS-PL requires extensive clin-
ical experience and instrument specific training. Diag-
nostic algorithms have not been computerized, so
diagnoses are formulated by expert judgement.
Translation and adaptation of Kiddie-SADS-PL
We followed the cross-cultural adaptation model used to
translate into Spanish and culturally adapt the Diag-
nostic Interview Schedule for Children (DISC) (19).
Even if cultural differences between American and
Icelandic children and adolescents may be to some
extent less important than between American and
Spanish-speaking child and adolescent populations, we
aimed at attaining cross-cultural equivalency by addres-
sing five important dimensions: semantic, technical,
criterion and conceptual.
This model provided the frame of reference employed
in the development of an Icelandic version of the K-
It involves the choice of terms and sentence structures
that ensure that the meaning of the source language
items is preserved in the translation. Semantic equiva-
lence can be achieved with a combination of translation
and back-translation techniques (20).
In our case, two different translaters have indepen-
dently translated and back-translated the instrument.
Following Geisinger’s recommendations (21), they are
fluent in both languages, knowledgeable about both
cultures and have a good understanding of clinical
characteristics and content that the instrument is
supposed to evaluate. Translation and back-translation
NORD J PSYCHIATRY �VOL 62 �NO 5 �2008 380
AN ICELANDIC VERSION OF THE KIDDIE-SADS-PL
drafts have been examined by a bilingual committee
composed of the two translaters and four bilingual and
experienced clinicians in child and adolescent psychiatry.
Feedback from interviewers after initial field testing was
essential in further improving the translation.
A few examples of differences between original and
back-translated instruments are following, illustrating
some of the semantic problems that had to be solved:
. Sadness/depressed mood;
. Separation from/absence of the mother;
. Racing/quick thoughts;
. Diurnal mood variations/daily mood fluctuations;
One difficulty consisted in that the English vocabulary is
broader and more detailed than the Icelandic one, which
in particular includes fewer words to describe emotions
The purpose here is to examine whether the content of
each item is meaningful to the population under study
and, if necessary, to remove some of them. In the
Icelandic version of Kiddie-SADS, we had for example
to remove ‘‘Walking on the train tracks’’, since transport
by train does not exist in Iceland. Additionally we had to
remove some references to famous US teenagers’ gangs,
as well as several examples of social games common with
American children and replace them by equivalent
Another issue in the field of content equivalence is to
determine whether the operationalization of what con-
stitutes normal behaviour is relevant to the culture under
study, with special consideration to evaluation of im-
pairment and social adaptation (normative equivalence).
Since Kiddie-SADS items include systematic estimation
of impairment or social adaptation, those issues have
been carefully examined by our bilingual committee.
The issues addressed in this field are related to under- or
over-reporting of certain problems by some cultural
groups compared to others (substance abuse, sexual
behaviour and thoughts, certain feelings). We considered
here the openness with which particular topics are
discussed by Icelandic teenagers, the manner in which
ideas are expressed and the way in which strangers
asking questions are treated. The most significant
particularity we described (but not systematically as-
sessed) was related to difficulties, showed in our
experience by many Icelandic boys, to express both
positive and negative emotions, especially anxiety.
This refers to the fact that the same theoretical construct
should be evaluated by the two versions of the assessment
instrument in the different cultures involved. Does the
concept operationalized in the source instrument (in-
dependently of the words and phrases used to represent
it) exist in the same form in the thinking of members of
the target culture?
In our case, two important discrepancies revealed by
differences between original and back-translated ver-
sions illustrated conceptual problems:
. Conduct/behavioural disorder;
. Attachment figure/someone close
The concept of attachment as it exists in English
semiology is almost impossible to translate into Icelandic.
Behling & Law (22) pointed out that translation/back-
translation was not an adequate test of the equivalence
of the target and source-language documents, but deals
only with semantic equivalence. The two versions may
correspond with one another for the wrong reasons and
target-language version may still not convey the in-
tended meaning to potential respondents.
Solving conceptual problems needs careful considera-
tion of: the constitutive definition of the concept of
interest, the theory that explains it and the nature of any
difference between the source and the target culture.
Usually this kind of equivalence cannot be directly
assessed except for rating scales with a known factorial
structure, which could be empirically tested with a
confirmatory factor analysis, trying to find the same
factor structure in the translated version.
Solving problems in that field involves identifying
pertinent norms in each culture and assessing when the
trait or disorder evaluated is said to exist according to
these norms. In our case, the culture for which Kiddie-
SADS is to be adapted is not very different from the
culture for which the instrument was developed and we
were not able to identify significant symptoms of mental
distress that would appear different culturally from those
included in the original version of the instrument.
However, we were aware of cultural differences in how
parents and professionals view behavioural problems.
In this study, we were not able to validate the
instrument against best estimate clinical judgement
from various Icelandic child and adolescent psychia-
trists, so we designed a study of the concurrent validity
using 11 well-known checklists and rating scales,
which had already been translated and validated in
Iceland and that assess several important dimensions of
psychopathology. This validation study will be the
subject of a separate paper.
NORD J PSYCHIATRY �VOL 62 �NO 5 �2008 381
B LAUTH ET AL.
The adolescent unit of the Department of Child and
Adolescent Psychiatry of the Landspı́tali University
Hospital in Reykjavı́k, is the only psychiatric ward for
adolescents in Iceland, admitting each year between 70
and 80 patients from 11 to 18 years of age, from all parts
of the country. The main reasons for admission are
severe behavioural or emotional disturbances with severe
functional impairment and often suicidality (61% of
cases in the period 2001�2004), 53% being acute admis-
sions. Mean length of stay was 43 days (2001�2004).
Adolescents presenting with alcohol and drug abuse as a
predominant problem are referred to other service
providers, such as social services. The population
admitted is culturally homogeneous and its geographic
distribution throughout the country is representative of
the general population for the same age categories.
Since the unit is the only facility in the country
providing psychiatric inpatient treatment for adoles-
cents, we assume that our population is representative
of the most severe range of psychiatric morbidity of the
adolescent clinical population in Iceland.
Fifteen subjects were included in the inter-rater relia-
bility data pool; the mean age was 15.2 (standard
deviation, s 1.0, range 14�17), 55% being females
and all were Icelandic.
These subjects were chosen at random among parti-
cipants in the validation study (n 86, mean age
15.0 years; s 1.34; range 11�18), females accounted
for 55.7% and again, all were Icelandic. They were
severely affected in most of the cases and some of them
could not complete the diagnostic interview.
As the main official diagnostic classification system in
European countries is ICD-10 for both clinical and
research purposes, results of Kiddie-SADS interviews
algorithms have been translated into the ICD-10. A few
additional questions were included in the interviews for
ICD-10 criteria not covered by the K-SADS-PL.
Both DSM-IV and ICD-10 diagnoses were generated,
and numbers of diagnostic criteria met were calculated
for the most frequent diagnostic categories in both
Two coders checked to verify accurate utilization of
DSM-IV and ICD-10 algorithms in the calculation of
numbers of diagnostic criteria met and assignment of
Inter-rater reliability was estimated with 15 interviews
being re-rated independently by other experienced and
trained clinicians. Three clinical psychologists and one
child and adolescent psychiatrist took part in the
project. Interviews were either videotaped or attended
at the same time by another rater.
The Statistical Package for Social Sciences was used for
data analysis (23). For comparisons of categorical
variables, chi-square tests were applied. Cohen’s Kappa
(24) was used for reliability measures. Criteria proposed
by Landis & Koch (24) were used to interpret the Kappa
coefficients: excellent reliability (Kappa 0.75), good
reliability (Kappa 0.59�0.75), fair reliability (Kappa
0.40�0.58) and poor reliability (KappaB0.40).
Kappa values were calculated in both classification
systems and for most frequent diagnostic categories. In
each diagnostic area, inter-rater reliability was also
examined at the symptom level, with Kappa values
calculated for each item. Correlations between numbers
of diagnostic criteria met generated by different K-
SADS raters were calculated.
Inter-rater reliability was also examined for main
diagnostic areas surveyed in the screen interview, in order
to estimate agreement in utilization of skip-out criteria.
Since several severely affected patients could not
complete the diagnostic interview, the number of sub-
jects allowing calculation of inter-rater reliability varied
according to diagnostic categories.
Inter-rater reliability of skip-out criteria
The average agreement evaluated by calculation of
Kappa statistics across the nine diagnostic categories
studied here is fair to excellent (Table 1).
Inter-rater reliability of diagnosis assignment
Kappas for diagnoses ranged from 0.31 to 1.0 (Table 2).
In each diagnostic category, inter-rater reliability was
also examined at the symptom level with Kappas
calculated for each item. Table 3 summarizes the results
Table 1. Inter-rater reliability: Agreement in utilization of
Diagnostic area in screen interview Kappa value n
Depressive disorders 1.00 15
Bipolar disorders 0.86 14
Attention-deficit/hyperactivity disorder 1.00 11
Oppositional defiant disorder 1.00 12
Conduct disorder 0.67 12
Post-traumatic stress disorder 1.00 8
Social phobia 1.00 12
Separation anxiety disorder 0.81 12
Generalized anxiety disorder 0.57 12
NORD J PSYCHIATRY �VOL 62 �NO 5 �2008 382
Table 2. Inter-rater reliability: measure of agreement on
Diagnostic category Kappa value n
Major depressive disorder (DSM-IV) 1.00 15
Melancholic depression (DSM-IV) 0.55 15
Dysthymia (ICD-10) 0.63 15
Moderate depressive episode (ICD-10) 0.32 15
Severe depressive episode (ICD-10) 0.44 15
Somatic syndrome (ICD-10) 0.47 15
Mania (DSM-IV) 0.31 14
Hypomania (DSM-IV) 1.00 14
Bipolar disorder not otherwise 0.44 14
Mania (ICD-10) 0.44 14
Hypomania (ICD-10) 1.00 14
ADHD*predominantly inattentive 0.81 11
ADHD*predominantly 1.00 11
hyperactive-impulsive type (DSM-IV)
ADHD*combined type 1.00 11
Oppositional defiant disorder (DSM-IV) 1.00 12
Oppositional defiant disorder (ICD-10) 1.00 12
Conduct disorder (DSM-IV and ICD-10) 1.00 12
Post-traumatic stress disorder (DSM-IV) 0.67 6
Post-traumatic stress 0.57 6
disorder*chronic type (DSM-IV)
Post-traumatic stress disorder (ICD-10) 0.67 6
Social phobia (DSM-IV) 0.82 12
Social anxiety disorder of 1.00 12
Separation anxiety disorder (DSM-IV) 1.00 12
Separation anxiety disorder of 1.00 12
Overanxious/generalized anxiety 1.00 12
Overanxious/generalized anxiety 0.82 12
ADHD, Attention-Deficit/Hyperactivity Disorder.
with average values calculated within each diagnostic
The inter-rater reliability data pool allowed calcula-
tion of correlations between numbers of diagnostic
criteria met generated by different K-SADS raters and
calculated in main areas of psychopathology, related to
both classification diagnostic systems. Statistically sig-
nificant correlations between different raters’ severity
scores were found at the 0.01 level in all diagnostic
categories (Table 4).
The translation and adaptation process of the Kiddie-
SADS-PL into the Icelandic language and culture aimed
at attaining cross-cultural equivalency by addressing five
important dimensions: semantic, technical, content,
criterion and conceptual.
The results of the study on inter-rater reliability must
be interpreted cautiously given the small size of the
AN ICELANDIC VERSION OF THE KIDDIE-SADS-PL
Table 3. Inter-rater reliability: average values at the symptom
level within each diagnostic category.
Diagnostic category Kappa value n
Depressive disorders 0.83 15
Bipolar disorders 0.85 14
ADHD*inattention 0.90 11
ADHD*hyperactivity-impulsivity 0.94 11
Oppositional defiant disorder 0.98 12
Conduct disorder 0.96 12
Post-traumatic stress disorder*current 0.93 9
Post-traumatic stress disorder*msp 0.86 3
Social phobia 0.48 12
Separation anxiety disorder 0.78 12
Generalized anxiety disorder 0.82 12
ADHD, Attention-Deficit/Hyperactivity Disorder msp, most severe
research sample. Additionally, two different measuring
procedures were used: in-session observation and video-
The data collected in this study were, however, in line
with those reported by other investigators (4, 12, 18, 25�
27). Agreement in utilization of skip-out criteria was
excellent for most diagnostic categories but moderate for
generalized anxiety disorder. Agreement in the assign-
ment of most frequent diagnostic categories was ex-
cellent, good or fair in most cases, but poor for moderate
depressive episode in ICD-10 diagnostic classification
system and for mania in both systems. Agreement was
excellent at the symptom level within each category
except Social Phobia. Correlations between different
raters’ severity scores were found significant at the 0.01
level in all diagnostic categories.
These results suggest that the translation and adapta-
tion work has provided an Icelandic version allowing
similar understanding among different raters and has
succeeded achieving acceptable equivalence.
The American version of the interview had shown
exceptional reliability at the symptom level (16). The
strongest reliability data were related to behavioural,
disruptive and affective disorders. The instrument had
shown poorer reliability for diagnosing anxiety disor-
ders. Our results are going in the same direction except
for anxiety disorders, with a tendency to show better
inter-rater reliability, and for bipolar spectrum disorders
(poorer reliability). Those difficulties concerning bipolar
spectrum disorders could be related to the fact that our
interviewers were less familiar to the assessment of this
kind of symptomatology.
Our findings also suggest a much poorer inter-rater
reliability for depressive disorders diagnosed in the ICD-
10 diagnostic classification system. This could be related
to the fact that diagnostic criteria are more numerous
and difficult to meet in the ICD-10 system, but this
could constitute a problem in Iceland, since results of
NORD J PSYCHIATRY �VOL 62 �NO 5 �2008 383
B LAUTH ET AL.
Table 4. Inter-rater reliability: correlation between numbers of
diagnostic criteria met.
Number of diagnostic criteria met Pearson’s value n
DSM-IV Depressive symptomatology/9 0.94** 15
ICD-10 depressive symptomatology/10 0.95** 15
DSM-IV Melancholic features/8 0.81** 15
ICD-10 somatic syndrome/8 0.85** 15
DSM-IV Manic symptomatology/8 0.93** 14
ICD-10 manic symptomatology/10 0.89** 14
ADHD Inattention 0.94** 11
(both classification systems)/9
ADHD Hyper-activity 0.98** 11
(both classification systems)/5
ADHD Impulsivity 0.76** 11
(both classification systems)/4
DSM-IV oppositional 1** 12
ICD-10 oppositional 0.98** 12
DSM-IV conduct disorder/15 0.77** 12
Social anxiety symptomatology 0.98** 12
Separation anxiety symptomatology 0.95** 12
(both classification systems)/8
DSM-IV generalized anxiety 0.98** 11
ICD-10 generalized anxiety 1** 12
DSM-IV post-traumatic stress 0.99** 6
ICD-10 post-traumatic stress 0.97** 6
**Correlation significant at the 0.01 level (two-tailed).
Kiddie-SADS interview algorithms have necessarily to be
translated into ICD-10. We conclude that further studies
are needed of differences between concurrent validity
data according to both diagnostic classification systems
as well as differences in diagnostic assignment procedures.
This initial inter-rater reliability study confirmed the
quality of translation and adaptation of the Kiddie-
SADS-PL and constitutes the first step of a larger
validation study of the Icelandic version of the instru-
Acknowledgements**This research was supported by the St Josefs
Spı́tali Research Foundation, by the Icelandic Center for Research
(RANNIS) and by the Wyeth Foundation for Psychiatric Research.
The authors would like to thank Brynjar Emilsson and Sigurður Rafn
Levy for their assistance in collecting inter-rater reliability data,
Guðmundur Skarphéðinsson for valuable statistical assistance, Gı́sli
Baldursson, Jón Skaptason, Ólafur Guðmundsson and Sigrún
Einarsdóttir for contribution to the translation and cross-cultural
adaptation study. We also want to thank Joan Kaufman, the author of
Kiddie-SADS-PL, as well as Á sgeir Haraldsson, Engilbert Sigurðsson
and Jón Grétar Stefánsson for their useful advice.
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Disorders and Schizophrenia for School-age Children*Present
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Bertrand Lauth, University of Iceland, Landspitali University
Hospital, Department of Child and Adolescent Psychiatry, Dalbraut
12, 105 Reykjavı́k, Iceland.
Páll Magnússon, Landspitali University Hospital, Department of
Child and Adolescent Psychiatry, Dalbraut 12, 105 Reykjavı́k, Iceland.
Pierre Ferrari, University Paris VI, Ecole Doctorale 3C, 9 quai St
Bernard, 75005 Paris, France.
Hannes Pétursson, University of Iceland, Landspitali University
Hospital, Division of Psychiatry, Hringbraut, 101 Reykjavı́k, Iceland.
NORD J PSYCHIATRY �VOL 62 �NO 5 �2008 385
Journal of Personality Assessment, 93(1), 26–32, 2011
Copyright C Taylor & Francis Group, LLC
ISSN: 0022-3891 print / 1532-7752 online
Reliability and Validity of the Spanish Version of the Minnesota
Multiphasic Personality Inventory–Adolescent (MMPI–A)
IHAB ZUBEIDAT,1 JUAN CARLOS SIERRA,2 JOSÉ MARÍA SALINAS,2 AND ANTONIO ROJAS-GARCÍA2
1Special Education Department, Sakhnin College for Teacher’s Education, Sakhnin, Israel
2Facultad de Psicologı́a, Universidad de Granada, Granada, Spain
The aim of this study was to determine the test–retest reliability and internal consistency of the scales of the Spanish version of the Minnesota
Multiphasic Personality Inventory–Adolescent (MMPI–A; Butcher et al., 1992). Two samples of 939 and 109 Spanish adolescents ages 14 to 18
years were assessed with the MMPI–A in their school environment. The frst sample responded to the inventory once, whereas the second sample
responded to it on 2 occasions with a 2-week interval between sessions. Results showed no signifcant differences in means or variances between the
frst and the second test administration for most MMPI–A scales. Test–retest reliability ranged between .62 (Amorality, Ma1) and .92 (Immaturity,
IMM); most correlations exceeded .70. Internal consistency values for the MMPI–A scales in the pretest and posttest were very similar overall.
External validity of the MMPI–A was demonstrated through several signifcant correlations between its scales and YSR/11–18 syndromes and social
interaction measures. The highest correlations were established between the Anxious/Depressed YSR/11–18 scale and other MMPI–A scales such
as Schizophrenia (Sc), Welsh’s Anxiety (A), Adolescent-Anxiety (A-anx) and Adolescent-Alienation (A-aln), and between the Social Avoidance
and Distress Scale and the MMPI–A Adolescent-Social Discomfort (A-sod) scale.
The Minnesota Multiphasic Personality Inventory–Adolescent
(MMPI–A; Butcher et al., 1992) is made up of 478 items that
assess a number of aspects of personality—up to 70 variables—
using different groups of scales: validity, clinical, content, and
supplementary scales, as well as subscales. The MMPI–A is
most frequently used in psychological, psychiatric, medical,
alcohol and drug treatment, and correctional clinical contexts.
It can be applied individually or in groups to adolescents ages
14 to 18 years.
Traditional validity scales, largely carried over from the orig-
inal MMPI (Hathaway & McKinley, 1943; Lie, L; Infrequency,
F; Infrequency 1 subscale, F1; Infrequency 2 subscale, F2; and
Defensiveness, K), help to detect deviant test-taking attitudes
and responses of adolescents. The Variable Response Inconsis-
tency (VRIN) and True Response Inconsistency (TRIN) scales
are additional validity scales that inform about the consistency
of responses to the items. With regards to the clinical scales
(Hypochondriasis, Hs; Depression, D; Hysteria, Hy; Psycho-
pathic Deviate, Pd; Masculinity-Femininity, Mf; Paranoia, Pa;
Psychasthenia, Pt; Schizophrenia; Sc; Hypomania, Ma; and
Social Introversion, Si), the revision from the MMPI to the
MMPI–A basically maintained the same items of the original
instrument, with the exception of Mf and Si. Six supple-
mentary scales were also included (MacAndrew Alcoholism
Scale–Revised, MAC–R; Alcohol/Drug Problem Acknowl-
edgment, ACK; Alcohol/Drug Problem Proneness, PRO;
Immaturity, IMM; Welsh’s Anxiety, A; and Repression, R),
Received November 20, 2008; Revised April 15, 2010.
Address correspondence to José Marı́a Salinas, Facultad de Psicologı́a, Uni-
versidad de Granada, 18071 Granada, Spain; Email: firstname.lastname@example.org
and 15 content scales were introduced (Adolescent-Anxiety,
A-anx; Adolescent-Obsessiveness, A-obs; Adolescent-
Depression, A-dep; Adolescent-Health Concerns, A-hea;
Adolescent-Alienation, A-aln; Adolescent-Bizarre Mentation,
A-biz; Adolescent-Anger, A-ang; Adolescent-Cynicism, A-
cyn; Adolescent-Conduct Problems, A-con; Adolescent-Low
Self-Esteem, A-lse; Adolescent-Low Aspirations, A-las;
Adolescent-Social Discomfort, A-sod; Adolescent-Family
Problems, A-fam; Adolescent-School Problems, A-sch; and
Adolescent-Negative Treatment Indicators, A-trt).
The item changes of the MMPI–A were made by the steer-
ing committee responsible for the creation of the revised test
booklet to improve the content and the relevance of some items
in the experiences of adolescents’ lives. Archer and Gordon
(1994) evaluated the impact of these changes. They examined
the psychometric stability of the modifed items using test–retest
correlations in a sample of 265 adolescents ages 13 to 17 years,
and found that the modifed items did not lead to any relevant
changes in response patterns compared to those on the MMPI.
Correlations between the basic scales of the original MMPI
have been studied in samples of adolescent inpatients by Archer,
Ball, and Hunter (1985), Archer and Gordon (1988), Archer,
Gordon, Anderson, and Giannetti (1989), Ball, Archer, Struve,
Hunter, and Gordon (1987), and Williams and Butcher (1989).
Butcher et al. (1992) reported the reliability of MMPI–A
clinical scale scores as ranging from .65 to .84 in a normative
sample of English-speaking adolescents (45 boys and 109 girls).
These values were similar to the test–retest correlation values
for adults presented in the MMPI–2 (Minnesota Multiphasic
Personality Inventory–2; Butcher, Dahlstrom, Graham, Telle-
gen, & Kaemmer, 1989) manual. Internal consistency values
(Cronbach’s alpha) of the MMPI–A validity and clinical scales
27 MMPI–A SPANISH VERSION RELIABILITY AND VALIDITY
in the normative sample of English-speaking boys and girls
were high for many scales (for example, Hs and Sc had an inter-
nal consistency of .78–.79 and .88–.89, respectively). Yet, the
coeffcients obtained for other scales such as Mf and Pa in the
same English-speaking sample were relatively low or moderate
(.40–.43 and .57–.59, respectively; Butcher et al., 1992).
The construction of scales focused on item content, such as
the MMPI–A content scales, has received increasing acceptance
over the last 30 years (Burisch, 1984; Jackson, 1971). Such
scales have proven to be as good at describing and predicting
personality variables as those created using other methods (Hase
& Goldberg, 1967). Moreover, their homogeneity makes them
easy to interpret (Burisch, 1984). The internal consistency of
the MMPI–A content scales was acceptable, both in the norma-
tive sample (α = .55–.83) and the clinical sample (α = .63–.83),
and test–retest correlations ranged between .62 and .82 (Butcher
et al., 1992). McGrath, Pogge, and Stokes (2002) studied the in-
cremental validity of the content scale scores when added to
the clinical scales of the MMPI–A as predictors of various be-
havioral disorders in a sample of adolescents of both sexes.
They found that the content scales offered incremental validity
over the clinical scales and supported the use of the content
scales as an adjunct to the traditional clinical scales. Forbey and
Ben-Porath (2003) reported that several of the MMPI–A content
scales show signifcant incremental validity in predicting behav-
ior and personality characteristics of adolescents. The clinical
scales also demonstrated incremental validity in reference to
the content scales, indicating that the two sets of scales provide
Because personality traits are expected to remain stable over
time, scores from instruments aimed at measuring such traits
should also remain very stable. Stability is usually assessed by
measuring the correlation between scores obtained in the same
test at two different points in time or scores obtained from paral-
lel forms of the same test. To estimate the reliability coeffcient
with the test–retest procedure, it is necessary to calculate the
Pearson product–moment correlation coeffcient between the
two sets of scores of the same individuals on two occasions.
However, this procedure has some drawbacks: (a) Repeating
the same test twice might cause the frst test to infuence the
results of the second one; and (b) a short time interval between
two test sessions might increase memory effects, whereas a
long time interval might lead to changes in the participants’
level of information. For all these reasons, estimates made with
the test–retest method are more appropriate for tests that assess
traits that are not likely to be affected by the effects of practice
and remain stable over the time interval in question. Informa-
tion about the degree of stability of scores is essential in many
In addition to test–retest stability, the stability of a given
measure might be low because there is a broad variation in
the amount of score change, or low internal consistency, across
scales. These two factors of instability can be reviewed by an-
alyzing the relation between the internal consistency reliability
coeffcient (Cronbach’s alpha) and the test–retest reliability co-
effcient through a qualitative procedure. So far, no statistic
available can be calculated and function as an indicator of the
type of relation between both coeffcients mentioned. If the same
test is applied twice with an interval of several weeks between
sessions, several scenarios could occur: Both the internal con-
sistency (alpha) and the test–retest reliability coeffcient might
be high or low and confrmed in the second test, or the former
might be high and the latter might be low; in the second case, the
test seems to be reliable, but the trait measured in participants
has changed in that time interval. Tests are meant to have a high
alpha coeffcient, showing adequate internal consistency. They
are also meant to show a high correlation between parallel forms
applied within an interval of weeks, showing adequacy in the
repeatability and stability of measures. So far, no studies have
analyzed the existing relation between the test–retest reliability
and internal consistency of the MMPI–A scales in the Spanish
The Spanish adaptation of the MMPI–A was carried out
´ by Jim´ omez Avila-Espada of the University ofenez-G´ and
Salamanca, Spain, between 1994 and 2002 and published in
2003 (Jim´ omez & ´ enez-G´ Avila-Espada, 2003); however, the au-
thors did not provide any information about the reliability of the
scales. No reliability coeffcients have been provided by other
studies that have used Spanish versions of the MMPI–A (Scott,
Butcher, Young, & Gomez, 2002; Scott & Mamani-Pampa,
2008). Given the scarcity of studies on the use of the MMPI–A
with Spanish adolescents, the aim of this study was to study
the test–retest reliability and internal consistency of MMPI–A
scale scores among Spanish adolescents (see Carretero-Dios &
P´ on, 2007, for instrumental studyerez, 2007; Montero & Le´
guidelines). External validity of MMPI–A scale scores was as-
sessed through their correlations with behavioral syndrome and
social interaction measures.
All data were obtained from Spanish students ages 14 to 18
years in various secondary schools of the province of Granada,
Spain. No nonstudent samples were used in this study, and par-
ticipants were assessed in their school environment. Of the 26
randomly selected secondary education schools whose partici-
pation was requested, only 13 agreed to participate in the study.
Thus, the sample was more a convenience sample than a random
sample. Participants were briefed in general terms about the pur-
poses of the research and told that privacy of the data collected
was guaranteed. All participants expressed their consent to par-
ticipate once the conditions of the study had been explained. The
assessment was carried out by a single examiner using standard
instructions and guidelines to answer the questionnaires.
Two nonoverlapping samples were selected: The frst one in-
cluded 939 adolescents (539 girls, 400 boys) with a mean age
of 15.69 years (SD = 1.27, range = 14–18); the second sample
was made up of 109 adolescents (53 girls, 56 boys) with a mean
age of 15.26 years (SD = 1.12, range = 14–17). About two
thirds (n = 630) of participants in the frst sample were in their
second, third, or fourth year of compulsory secondary education
(Educacion´ Secundaria Obligatoria); the rest were students in
the frst or second year of noncompulsory secondary education
(Bachillerato; n = 174) and students following various voca-
tional training courses (Ciclos Formativos; n = 135) such as
cooking, hairdressing, and so on.
MMPI–A (Butcher et al., 1992). MMPI–A valid-
ity, clinical, content, and supplementary scales, and
subscales of the clinical scales, were examined in this study.
28 ZUBEIDAT, SIERRA, SALINAS, ROJAS-GARCIA
Youth Self-Report for Ages 11–18 (YSR; Achenbach &
Rescorla, 2000, 2001). The YSR assesses adolescents’ psy-
chosocial skills and problem behaviors. Verhulst, van der Ende,
and Koot (1997) provided evidence of reliability and validity
data. These authors reported Cronbach alpha values of .61 for
boys and .67 for girls in a sample of normal adolescents (15–
18 years). Higher values were found in samples of adolescent
patients: boys (.73) and girls (.70). In Spain, Lemos, Fidalgo,
Calvo, and Menéndez (1992) reported that girls scored higher
than boys on internalized behaviors, whereas boys scored higher
on externalized behaviors. Abad, Forns, Amador, and Martorell
(2000) revealed that internal consistency is higher for internal-
ized and externalized syndrome scales (range = .81–.84) than
narrowband ones (range = .56–.74).
Liebowitz Social Anxiety Scale (LSAS; Liebowitz, 1987).
This scale includes 24 items that assess performance in so-
cial situations by evaluating the degree of fear experienced and
the degree of avoidance reported by participants. Cox, Ross,
Swinson, and Direnfeld (1998) reported high internal consis-
tency coeffcients for the social fear and social avoidance sub-
scales (α = .90). In the Spanish validation, Bobes et al. (1999)
obtained internal consistency coeffcient values above .73 for all
the LSAS scales; the intraclass correlation coeffcients obtained
in the 2-week test–retest studies featured values above .82 for
Social Interaction Anxiety Scale (SIAS; Mattick & Clarke,
1998). The SIAS includes 20 items that are meant to be an-
swered using a 5-point Likert scale. It has a high internal consis-
tency (α = .93) and a 1-month test–retest correlation coeffcient
above .90. Ries et al. (1998) reported that the SIAS discriminates
between generalized and specifc subtypes of social phobia. In
Spain, Olivares, Garcı́a-López, and Hidalgo (2001) found an
internal consistency coeffcient of .89 and obtained two factors
that explain 40.11% of the variance. Nevertheless, the confr-
matory factor analysis supported the single-factor model and
clustered all the items into a single factor called interaction
Social Avoidance and Distress Scale (SAD; Watson &
Friend, 1969). The SAD includes 28 items, half of which
refer to subjective discomfort in social situations, and the other
half of which refect active avoidance of such situations. This
scale has shown an internal consistency of .94 and a 1-month
test–retest reliability of .68. Hoffmann, DiBartolo, Holaway, and
Heimberg (2004) reported a Cronbach’s alpha of .93. In Spain,
the reliability of the avoidance subscale was .87, whereas that
of social anxiety was .85 (Comeche, Dı́az, & Vallejo, 1995).
Garcı́a-López, Olivares, Hidalgo, Beidel, and Turner (2001)
found a 10-day test–retest reliability of .85 in an adolescent
Fear of Negative Evaluation Scale (FNE; Watson &
Friend, 1969). The FNE assesses the degree of intensity with
which individuals experience fear of being negatively evaluated
by others. Watson and Friend (1969) reported an internal con-
sistency coeffcient of .94 and a 1-month test–retest reliability of
.78. In Spain, internal consistencies of .94 and .90 were obtained
for the original and the short versions of the scale, respectively.
Garcia-López et al. (2001) reported a 10-day test–retest relia-
bility of .84.
The 939 adolescents were assessed collectively in their class-
rooms in two 75-min sessions by a single examiner. The re-
maining 109 adolescents were assessed in two different ses-
sions separated by a 2-week interval. Data collection started
once consent had been obtained from the parents and teach-
ers of the adolescents and the adolescents themselves. They
were all assured of confdentiality. Each session lasted for about
60 min and the MMPI–A was administered in group testing by
the same examiner. The assessment of the sample of 939 ado-
lescents with all measures occurred over a 4-month period, and
that of the sample of 109 adolescents twice with the MMPI–A
took 2 weeks. All participants were offered the opportunity to
receive individual information about their results on the tests as
well as their psychological interpretation.
The assumptions of classical test theory were tested by veri-
fying whether the means and variances of the variables differed
signifcantly between the frst and the second administration of
the MMPI–A in the sample of 109 adolescents.
Hotelling’s T2 test for equality of means was not signif-
icant for the 67 variables, with the exception of VRIN and
TRIN, F (67, 32) = 1.36, p = .171. Equality of variances was
tested by the Pitman–Morgan test with the Bonferroni correc-
tion for the same 67 variables. No signifcant differences were
obtained between variances obtained in the two administra-
MMPI–A test–retest reliability coeffcients in the sample of
109 adolescents ranged from .62 (for the Ma1scale) to .92 (for
the IMM scale); most correlations exceeded .70. Alpha internal
consistency values were similar in both administrations of the
test. Alpha and test–retest correlation values were similar in
most cases; low internal consistency values and high test–retest
correlations were only obtained for 18 scales (see Table 1).
The internal consistency of both administrations of the
MMPI–A in the sample of 109 adolescents was also calculated.
As shown in Table 1, pretest and posttest alpha values in this
sample were very similar to those obtained in the initial sample
of 939 adolescents.
Analysis of external validity data for the MMPI–A involved
calculating the correlations between the basic and content scales
and the common seven syndromes of the YSR/11–18 found in
both boys and girls in the factorial study of Zubeidat, Fernández-
Parra, Salinas, and Sierra (in press) and other social anxiety mea-
sures (LSAS, SIAS, SAD, and FNE). Results are shown in Ta-
ble 2. Overall, correlations were moderate in size. The strongest
relationships were found between MMPI–A scales assessing
social introversion/discomfort and social anxiety measures,
and between MMPI–A scales measuring anxiety and depres-
sion and the Anxious/Depressed scale of the YSR/11–18 (see
As discussed by Archer (2005), the MMPI and the MMPI–
A have been used in the assessment of adolescents for over
60 years, leading to more than 200 studies dealing with
29 MMPI–A SPANISH VERSION RELIABILITY AND VALIDITY
TABLE 1.—Test–retest reliability and internal consistency in both administrations of the Minnesota Multiphasic Personality Inventory–Adolescent.
Alpha of Initial
Scale No. of Items Test–Retestr Pretest Alpha Posttest Alpha Sample (N = 939)
Variable Response Inconsistency (VRIN) 50 .80 .43 .74 .60
True Response Inconsistency (TRIN) 24 .81 — — —
Infrequency Subscale (F1) 34 .75 .80 .84 .81
Infrequency Subscale (F2) 33 .89 .84 .85 .83
Infrequency (F) 67 .92 .89 .91 .89
Lie (L) 14 .81 .45 .46 .58
Defensiveness (K) 30 .77 .70 .73 .65
Hypochondriasis (Hs) 31 .81 .74 .75 .71
Depression (D) 57 .74 .56 .46 .57
Hysteria (Hy) 60 .71 .53 .57 .60
Psychopathic Deviate (Pd) 48 .85 .64 .58 .54
Masculinity/Femininity-Males (Mf) 44 .74 .36 .32 .27
Masculinity/Femininity-Females (Mf) 44 .80 .24 .09 .20
Masculinity-Femininity (Mf) 44 .86 — — —
Paranoia (Pa) 40 .77 .54 .55 .62
Psychasthenia (Pt) 48 .92 .85 .85 .84
Schizophrenia (Sc) 77 .90 .89 .89 .87
Hypomania (Ma) 46 .82 .69 .64 .61
Social Introversion (Si) 62 .88 .80 .77 .70
Subjective Depression (D1) 29 .76 .67 .60 .64
Psychomotor Retardation (D2) 14 .66 .21 .18 .18
Physical Malfunctioning (D3) 11 .68 .11 .34 .34
Mental Dullness (D4) 15 .79 .63 .55 .55
Brooding (D5) 10 .71 .57 .48 .62
Denial of Social Anxiety (Hy1) 6 .75 .57 .58 .56
Need for Affection (Hy2) 11 .78 .54 .63 .35
Lassitude-Malaise (Hy3) 15 .83 .61 .59 .60
Somatic Complaints (Hy4) 17 .78 .69 .67 .58
Inhibition of Aggression (Hy5) 7 .68 .15 .20 .36
Familial Discord (Pd1) 9 .80 .65 .60 .45
Authority Problems (Pd2) 8 .65 .20 .34 .22
Social Imperturbability (Pd3) 6 .83 .58 .56 .42
Social Alienation (Pd4) 12 .78 .45 .39 .50
Self Alienation (Pd5) 12 .80 .62 .61 .54
Persecutory Ideas (Pa1) 17 .78 .74 .75 .69
Poignancy (Pa2) 9 .77 .34 .36 .44
Naivete (Pa3) 9 .79 .40 .53 .49
Social Alienation (Sc1) 21 .80 .65 .72 .68
Emotional Alienation (Sc2) 11 .83 .52 .43 .56
Lack of Ego Mastery-Cognitive (Sc3) 10 .84 .68 .60 .60
Lack of Ego Mastery-Conative (Sc4) 14 .80 .54 .58 .56
Lack of Ego Mastery-Defective Inhibition (Sc5) 11 .81 .61 .63 .60
Bizarre Sensory Experiences (Sc6) 20 .82 .77 .75 .70
Amorality (Ma1) 6 .62 .14 .16 .18
Psychomotor Acceleration (Ma2) 11 .79 .49 .49 .40
Imperturbability (Ma3) 8 .76 .40 .52 .12
Ego Infation (Ma4) 9 .74 .49 .45 .43
Shyness/Self-Consciousness (Si1) 14 .86 .75 .74 .66
Social Avoidance (Si2) 8 .82 .61 .61 .55
Alienation-Self and Others (Si3) 17 .82 .74 .69 .70
MacAndrew Alcoholism Scale-Revised (MAC-R) .49 .78 .38 .54 .46
Alcohol/Drug Problem Acknowledgment (ACK) 13 .88 .65 .66 .62
Alcohol/Drug Problem Proneness (PRO) 36 .85 .50 .45 .48
Immaturity (IMM) 43 .92 .83 .81 .75
Welsh’s Anxiety (A) 35 .90 .84 .81 .84
Repression (R) 33 .81 .51 .53 .61
Adolescent-Anxiety (A-anx) 21 .90 .75 .74 .67
Adolescent-Obsessiveness (A-obs) 15 .82 .63 .61 .67
Adolescent-Depression (A-dep) 26 .86 .78 .76 .78
Adolescent-Health Concerns (A-hea) 37 .86 .84 .83 .77
Adolescent-Alienation (A-aln) 20 .88 .71 .75 .70
Adolescent-Bizarre Mentation (A-biz) 19 .87 .81 .82 .74
Adolescent-Anger (A-ang) 17 .85 .71 .71 .66
Adolescent-Cynicism (A-cyn) 22 .86 .74 .78 .69
Adolescent Conduct Problems (A-con) 23 .89 .68 .74 .70
Adolescent-Low Self-Esteem (A-lse) 18 .86 .66 .63 .65
Adolescent-Low Aspirations (A-las) 16 .85 .65 .59 .44
Adolescent-Social Discomfort (A-sod) 24 .91 .77 .76 .71
Adolescent-Family Problems (A-fam) 34 .90 .86 .84 .78
Adolescent-School Problems (A-sch) 20 .83 .66 .66 .63
Adolescent-Negative Treatment Indicators (A-trt) 26 .86 .75 .77 .70
30 ZUBEIDAT, SIERRA, SALINAS, ROJAS-GARCIA
TABLE 2.—Pearson’s correlations between Minnesota Multiphasic Personality Inventory–Adolescent clinical and content scales and Youth Self-Report for Ages
11–18 scales and social anxiety measures.
Scale A/D DB AB SC THP RP AP LSAS SIAS SAD FNE
Infrequency Subscale (F1) .14** .29** .08* −.02 .23** −.10** .16** .01 .09** .16** .02
Infrequency Subscale (F2) .18** .22** .10** .04 .25** −.02 .15** .13** .16** .23** .08*
Infrequency (F) .17** .28** .10** .01 .27** −.06 .17** .08* .14** .22** .06
Lie (L) −.28** −.27** −.32** −.18** −.27** −.21** −.27** −.20** −.12** −.06 −.10**
Defensiveness (K) −.43** −.32** −.41** −.33** −.38** −.29** −.33** −.32** −.28** −.26** −.25**
Hypochondriasis (Hs) .26** .21** .17** .28** .23** −.01 .12** .14** .20** .29** .20**
Depression (D) .29** .01 .01 .05 .06 .06 −.08* .17** .32** .34** .31**
Hysteria (Hy) .11** .06 .01 .10** .04 −.16** −.05 −.04 .01 .08* .06
Psychopathic Deviate (Pd) .38** .38** .28** .14** .33** −.00 .24** .11** .13** .20** .15**
Masculinity-Femininity (Mf) .20** −.05 .12** .13** .00 .03 −.09* .06 .11** .01 .21**
Paranoia (Pa) .28** .23** .15** .11** .24** −.05 .13** .08* .17** .23** .21**
Psychasthenia (Pt) .54** .36** .36** .35** .43** .28** .31** .38** .39** .41** .36**
Schizophrenia (Sc) .37** .37** .27** .21** .41** .09** .30** .21** .25** .33** .19**
Hypomania (Ma) .17** .37** .26** .16** .33** −.03 .31** .04 −.01 −.01 −.02
Social Introversion (Si) .38** .15** .14** .15** .17** .35** .13** .43** .54** .60** .41**
Welsh’s Anxiety (A) .55** .33** .36** .37** .41** .31** .31** .42** .42** .40** .39**
Repression (R) −.19** −.30** −.28** −.21** −.31** −.13** −.32** −.14** .01 .03 −.01
Adolescent-Anxiety (A-anx) .49** .35** .36** .37** .41** .21** .29** .32** .30** .34** .33**
Adolescent-Obsessiveness (A-obs) .41** .31** .36** .33** .36** .28** .32** .33** .32** .30** .28**
Adolescent-Depression (A-dep) .55** .31** .29** .24** .36** .19** .22** .28** .33** .34** .31**
Adolescent-Health Concerns (A-hea) .19** .18** .13** .23** .23** −.06 .12** .10** .15** .26** .18**
Adolescent-Alienation (A-aln) .39** .29** .19** .11** .31** .12** .19** .21** .32** .36** .19**
Adolescent-Bizarre Mentation (A-biz) .26** .34** .22** .19** .38** .02 .29** .08* .11** .19** .06
Adolescent-Anger (A-ang) .34** .44** .49** .27** .36** .18** .36** .22** .16** .20** .16**
Adolescent-Cynicism (A-cyn) .31** .28** .27** .21** .32** .15** .28** .22** .12** .14** .12**
Adolescent Conduct Problems (A-con) .11** .43** .22** .10** .27** .01 .32** .06 .03 .12** −.05
Adolescent-Low Self-Esteem (A-lse) .44** .24** .20** .19** .26** .22** .20** .35** .40** .40** .33**
Adolescent-Low Aspirations (A-las) .13** .17** .12** .03 .10** .03 .10** .07* .15** .19** .07*
Adolescent-Social Discomfort (A-sod) .19** .09** −.01 .00 .06 .23** .04 .30** .46** .53** .23**
Adolescent-Family Problems (A-fam) .28** .36** .27** .09** .34** .02 .26** .09** .13** .17** .08*
Adolescent-School Problems (A-sch) .20** .44** .23** .12** .27** .06 .22** .11** .09** .14** .04
Adolescent-Negative Treatment Indicators (A-trt) .38** .30** .24** .17** .32** .23** .25** .34** .34** .37** .21**
Note. A/D = Anxious/Depressed; DB = Delinquent Behavior; AB = Aggressive Behavior; SC = Somatic Complaints; THP = Thought Problems; RP = Relational Problems;
AP = Attention Problems; LSAS = Liebowitz Social Anxiety Scale; SIAS = Social Interaction Anxiety Scale; SAD = Social Avoidance and Distress Scale; FNE = Fear of Negative
∗ p < .05. **p < .01.
adolescent samples. Such studies have made important con-
tributions not only to the study of the psychometric charac-
teristics of these instruments, but also to our understanding of
the development and psychopathology of adolescents. How-
ever, the characteristics of these tools have not been suff-
ciently studied in certain adolescent populations. For example,
Perfect (2005) pointed out that there are still limited em-
pirical data to support the clinical use of the MMPI–A in
samples of abused adolescents. Similarly, no studies so far
have explored the test–retest reliability and the internal con-
sistency of the scales of the MMPI–A in the Spanish adolescent
The design of studies with the objectives just mentioned often
involves working with two samples: The frst one was a large
reference sample with participants assessed in one session, and
the second and smaller sample was assessed twice with the same
test, with a 2-week time interval between administrations. To
estimate the reliability coeffcient with the test–retest method,
the test should measure traits that are not likely to be affected by
the effects of practice and remain stable over the time interval
in question. Thus, it is necessary to verify the stability of the
score distribution beforehand. Results of this study showed no
overall differences between the means of the frst and second
administration of the MMPI–A scales; results of the multivariate
difference of means test were clearly not signifcant. Likewise,
no signifcant differences were found in the variances of both
administrations of the MMPI–A.
With regard to test–retest reliability, correlations between
both administrations of the MMPI–A scales were high and were
considered satisfactory. In fact, most of these correlations ex-
ceeded .70 and ranged between .62 and .92. These results are
similar to those found by P´ ıas, Dur´ omez-erez y Far´ an, and G´
Maqueo (2003) in a sample of 1,056 Mexican adolescents,
where test–retest correlations were statistically signifcant with
values ranging between .36 and .90. They also agree with those
obtained by Butcher et al. (1992), which ranged between .47
and .84 in a sample of American adolescents. P´ ıaserez y Far´
et al. (2003) concluded that the clinical, validity, content, and
supplementary scales of the MMPI–A were stable in their sam-
ple of adolescents, like other studies (Aharoni, 1999; Ampudia,
Duran, & Lucio, 1995; Gomez, Johnson, Davis, & Velazquez,
2000; Hammel, 2001; Mendoza-Newman, 2000; Sirigati, 2000),
including this one. Moreover, alpha values were very simi-
lar across the pretest and posttest. Along these lines, Carlson
and Hofstra (2001) carried out a study in which 80 adoles-
cents between the ages of 14 and 18 completed a computerized
and a written version of the MMPI–A (with a 1-week interval
between both counterbalanced sessions); results showed that
the clinical, content, and supplementary scales and the test–
retest correlation coeffcients were statistically signifcant and
31 MMPI–A SPANISH VERSION RELIABILITY AND VALIDITY
compared favorably with the reliability data provided in the
MMPI–A manual. Results from Stein, McClinton, and Gra-
ham’s (1998) study examining the long-term stability of the
clinical, content, and supplementary scales and the MMPI–A
personality psychopathology scales in a sample of 61 adoles-
cents were also consistent with the fndings of MMPI–A score
reliability reported earlier. Moreover, improvements shown dur-
ing the development of the MMPI–A have led to moderate in-
creases in the stability of the clinical scales in adolescents.
Findings on internal consistency values and test–retest cor-
relation showed that both coeffcients were similar, and could
therefore be viewed as jointly providing evidence of suffcient
consistency as well as stability in responses to the items. In
fact, Vinet and Alarcon´ (2003) studied a sample of 705 Chilean
adolescents and reported that the MMPI–A is a stable and con-
sistent measure, with similar reliability levels (stability and in-
ternal consistency) to those obtained in studies carried out in
other countries. Low internal consistency and high test–retest
correlations were only obtained in a few scales of this study,
demonstrating the overall stability of responses to the items.
However, the inadequate internal consistency of these scales
shows that they need to be reviewed. Problems related to lack of
internal consistency cannot be attributed to sample size, because
values in the smaller sample of 109 adolescents were very sim-
ilar to those obtained in the sample of 939 adolescents. We also
studied the external validity of the clinical and content MMPI–A
scales based on their correlation with other variables related to
adolescents’ behavioral problems and social discomfort. Over-
all, most of these correlations were signifcant and moderate
in size, and in the expected direction. In general, MMPI–A
scales that assess internalized problems showed higher corre-
lations with YSR/11–18 scales that assess such problems than
with those assessing externalized problems; conversely, scales
that assess externalized problems show higher correlations with
YSR/11–18 scales related to externalized problems rather than
internalized ones. These results are similar to those found in
other MMPI–A studies with clinical samples. Indeed, Butcher
et al. (1992) reported similar correlations between the clinical
scales and the Child Behavior Checklist in the MMPI–A manual.
More recently, Veltri et al. (2009) obtained similar results with
psychiatric and forensic samples by correlating the MMPI–A
scales with criterion variables using a standardized Record Re-
view Form; the study by Stokes, Pogge, Sarnicola, and McGrath
(2009) in an adolescent inpatient psychiatric sample showed a
Nevertheless, the highest correlations were only found be-
tween MMPI–A social interaction scales and social anxi-
ety variables and between MMPI–A anxiety and depression
scales and the anxious/depressed syndrome. Likewise, Mennin,
Heimberg, and Jack (2000) reported that individuals with patho-
logical levels of social anxiety show high scores of social anxiety
and avoidance, general anxiety, cognitive symptoms of anxiety,
and depressive mood. Also, Heimberg et al. (1999) found that
total anxiety and avoidance scores highly correlated with total
fear and total avoidance (.90 for both); these authors reported
that the correlations found between total anxiety and avoidance
and other measures of anxiety tend to be higher than those found
between the former and measures of depression, as happened
in this study. Along these lines, Zubeidat, Salinas, and Sierra
(2008) reported that total anxiety and avoidance scores showed
higher correlations with measures of social anxiety (e.g., SIAS,
FNE, and SAD) than with variables related to MMPI–A depres-
sion scales (e.g., Depression-D and Depression-DEP). Overall,
the strongest support in this study is found for MMPI–A scales
related to depression, anxiety, and social discomfort.
This study does not include a sample of adolescents not at-
tending school, which limits the possibilities of generalizing the
results beyond the population of adolescent students. In Spain,
education is compulsory until the age of 16, and there are very
few adolescents not attending school or marginalized in the
age range between 16 and 18 years. Also, participants in this
study do not represent a strictly random sample because they
were selected by convenience sampling. The results therefore
cannot be considered representative of the Spanish adolescent
population, and further study in clinical adolescent samples is
certainly needed. A fnal drawback is the fact that the stability of
the measures of the MMPI–A was only studied with a test–retest
analysis of two points in time.
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