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Neurocognitive dimensions characterising patients with first-episode psychosis

Published online by Cambridge University Press:  02 January 2018

S. Friis,
K. Sundet,
B. R. Rund,
P. Vaglum and
T. H. Mcglashan
S. Friis*
Affiliation:
University of Oslo, Norway
K. Sundet
Affiliation:
Rikshospitalet University Hospital, Oslo, Norway
B. R. Rund
Affiliation:
University of Oslo, Norway
P. Vaglum
Affiliation:
University of Oslo, Norway
T. H. Mcglashan
Affiliation:
Yale University USA
*
Professor Svein Friis, Department of Research and Education, Division of Psychiatry, Ullevål University Hospital, N-0407 Oslo, Norway Tel: +47 22 11 84 40; fax: +47 22 11 78 48; e-mail: svein.friis@psykiatri.uio.no
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Abstract

Background

Assessment of neurocognitive dysfunction in schizophrenia is hampered by the multitude of tests used in the literature.

Aims

We aimed to identify the main dimensions of an assessment battery for patients with first-episode psychosis and to estimate the relationship between dimension scores and gender, age, education, diagnosis and symptoms.

Method

Eight frequently used neuropsychological tests were used. We tested 219 patients 3 months after start of therapy or at remission, whichever occurred first.

Results

We identified five dimensions: working memory (WM); verbal learning (VL); executive function (EF); impulsivity (Im); and motor speed (MS). Significant findings were that the MS score was higher for men, and the WM and VL scores were correlated with years of education.

Conclusions

Neurocognitive function in first-episode psychosis is described by at least five independent dimensions.

Information

Type
Papers
Information
The British Journal of Psychiatry , Volume 181 , Issue S43: European First-Episode Schizophrenia Network , September 2002, pp. s85 - s90
Copyright
Copyright © Royal College of Psychiatrists, 2002 

Subgroups of patients within the psychotic spectrum are characterised by differences in behavioural and affective, as well as cognitive, symptom profiles. Neuropsychological deficits are recognised as a core determinant of the illness (Reference GreenGreen, 1998; Reference Rund and BorgRund & Borg, 1999; Reference Bilder, Goldman and RobinsonBilder et al, 2000) but concept terminology and assessment methods still remain unsettled issues. Factor analysis is a potent technique for reducing a number of measures into a smaller set of uncorrelated dimensions (Reference Lieh-Make and LeeLieh-Make & Lee, 1997). The complexity of the component structure depends on the number of tests included and the clinical characteristics of the group studied (Reference Bechtoldt, Benton and FogelBechtoldt et al, 1962; Reference Heaton, Grant and ButtersHeaton et al, 1995).

In this paper we present the results of eight neuropsychological tests in a group of stabilised patients with first-episode psychosis. We used data-reducing techniques to try to identify the main dimensions of an assessment battery for a group of patients with first-episode psychosis. We wanted to answer the following questions:

  1. (a) To what extent are the scores of different neurocognitive tests intercorrelated?

  2. (b) Can we meaningfully combine the test scores into a fairly small number of dimension scores?

  3. (c) To what extent are these dimension scores intercorrelated?

  4. (d) To what extent are they related to patient age, gender, education, diagnosis or symptoms?

METHOD

The study is part of a multi-site investigation of the relationship between duration of untreated psychosis (DUP) and outcome. The study is carried out in four sites, two (Stavanger and Haugesund in Norway) with an early detection programme and two (Ullevål sector in Oslo, Norway and Roskilde, Denmark) with an ordinary detection programme. All patients gave written informed consent. The regional ethics committee has approved the study. On admission, the patients were diagnosed according to DSM-IV (American Psychiatric Association, 1994) by special assessment teams, and rated on scales including a split Global Assessment of Functioning (GAF) scale that gave separate scores for symptoms and function. At 3 months GAF was scored again. Treatment was initiated according to a standard protocol, including neuroleptic medication, individual, supportive psychotherapy and multi-family groups. Further details are given by Johannessen et al (Reference Johannessen, McGlashan and Larsen2001) and Larsen et al (Reference Larsen, McGlashan and Johannessen2001).

Subjects

This paper is based on a sample of 219 patients. Diagnostic and demographic characteristics and symptom scores at 3 months are presented in Table 1.

Table 1

Demographic variables and symptom scores

Gender
Male (n) 125
Female (n) 94
Diagnoses
Core 1511
Non-core 682
Age (mean, s.d.) 27.9 (9.4)
Education (years) (mean, s.d.) 12.1 (2.7)
GAF at 3 months
Symptoms 47.4 (12.7)
Function 49.0 (12.2)

Because our intention was to measure neurocognitive traits and not be biased by acute effects of the psychotic episode, patients were tested 3 months after start of therapy or at remission, whichever occurred first. As seen from Table 1, this strategy seems to have been successful as the symptom level was fairly low at 3 months.

Neurocognitive tests

Eight neuropsychological tests were chosen for assessing neurocognitive function. We selected elected tests used frequently and shown to be sensitive for diagnostic and prognostic issues in schizophrenia. The tests were administered by a trained test technician or approved neuropsychologist. The tests were administered in the following order.

California Verbal Learning Test (CVLT)

The CVLT (Reference Delis, Kramer and KaplanDelis et al, 1987) measures capacity for explicit verbal memory. The test consists of oral presentation of a 16-word ‘shopping list’ (list A) for five immediate recall trials, followed by a single presentation and recall of a second 16-word ‘interference’ list (list B). The words on both lists consist of four items from each of four categories. Free- and category-cued recall of list A is elicited immediately after recall of list B (short delay) and again 20 minutes later (long delay). Finally, a recognition trial is run, involving oral presentation of 44 ‘shopping items’ of which subjects are asked to identify the 16 list A items. Scoring of the test involves computing several parameters of learning strategies in addition to the number of words recalled at the various stages of learning. Based on scores from 286 normal subjects and 113 neurological patients, Delis et al (Reference Delis, Freeland and Kramer1988) found support for a 6-component model of the CVLT. Subsequent research has confirmed the multi-dimensional nature of the test (e.g. Reference Vanderploeg, Schinka and RetzlaffVanderploeg et al, 1994) and has suggested qualitative differences in the way psychiatric patients solve the task compared with normal controls (Reference Kareken, Moberg and GurKareken et al, 1996). Our study did not involve computerised scoring of test protocols and only measures of immediate and delayed recall, recognition, perseverations and intrusions are reported.

Backward Masking Test (BMT)

The BMT (Reference Spaulding, Hargrove and CrineanSpaulding et al, 1981; Reference RundRund, 1993; Green et al, Reference Green, Neuchterlein and Mintz1994a ,Reference Green, Neuchterlein and Mintz b ) assesses the earliest phases of visual information processing. A standard target duration procedure in which pairs of digits (target stimuli) are presented for 16.5 ms on the monitor was used. The stimuli are followed by a patterned mask of Xs of equal duration, covering the image of the digits on the monitor. The task consists of 30 stimulus presentations: 10 with a 33 ms stimulus onset mask (short); 10 with a 49.5 ms stimulus onset mask (long); and 10 with no mask. The three test trials are assigned randomly. Identification of each digit in the pair is scored separately, yielding a maximum score of 20 correct for each of the three conditions. In the present report, the no-mask condition is excluded for the final analysis and the mean of the two mask conditions are used in order to improve the reliability of the measure.

Finger Tapping Test (FTT)

The FTT (Reference LezakLezak, 1995) requires that the subject tap as rapidly as possible with the index finger on a small lever, which is attached to a mechanical counter. The test is basically a test of simple motor speed, although some degree of coordination is required. The subject is given 5 consecutive 10-s trials with the preferred hand and then 5 consecutive trials with the non-preferred hand. Mean number of taps for each hand is computed. Because no lateralised motor deficits were expected, mean score of the two hands are used in the component analysis.

Wisconsin Card Sorting Test (WCST)

The WCST (PC-version, Reference Heaton, Chelune and TalleyHeaton et al, 1993) is a test of abstract thinking that requires the ability to form a hypothesis and check it out. The test is the most commonly used measure of executive functioning in schizophrenia research (Reference GreenGreen, 1998) and provides estimates of perseverative thinking and distractibility. The subject is asked to sort a series of cards to one of four key cards that vary in shape, colour and number of shapes. Feedback after each response provides information whether or not the correct matching rule is being followed. After 10 consecutive correct sorts, the test shifts without warning to reinforce a new sorting rule. The test terminates after 128 trials or when the subject has completed the three correct sorting rules twice. Studies by Bell et al (Reference Bell, Conway and Kaplan1997) and Koren et al (Reference Koren, Seidman and Harrison1998) find evidence for a three-factor structure in the WCST (perseveration, idiosyncratic sorting/non-perseverative errors and failure to maintain set). The same pattern is generally concluded in normal control subjects or subjects with traumatic brain injuries (Reference Wiegner and DondersWiegner & Donders, 1999). Recent research has suggested that impaired scores may be explained by reduced intellectual capacity rather than executive dysfunction (Reference LawsLaws, 1999) but the cause-and-effect question has still to be solved.

Controlled Oral Word Association task (COWA)

The COWA (Reference Spreen and StraussSpreen & Strauss, 1998) is a measure of verbal fluency requiring the ability to generate words beginning with specific letters (F, A and S) for 1 minute each. The instructions followed are identical to those used by Spreen & Benton (Reference Spreen and Benton1969).

Trail Making Test (TMT)

The TMT (Reference LezakLezak, 1995) consists of two parts (A and B). Each part measures speed of visual scanning with a motor component. Part A requires the subject to connect series of numbered circles arrayed randomly on a sheet of paper using a pencil. In part B the array consists of both numbers and letters, and the subject must connect them in alternating order. Part B demands simultaneous processing capacity for two sets of mental operations (number and letter sequencing) as well as a rule-following instruction to alternate between the sets. It is a sensitive measure of disturbances in both attention and executive function.

Digit Span Distractibility Test (DSDT)

In the DSDT (Reference Oltmanns and NealeOltmanns & Neale, 1975; Reference RundRund, 1983) the subjects hear short strings of digits with and without distractors and are asked to recall the digits in correct order. The test measures short-term memory, selective attention and distractibility. Neutral and distractor items are interspersed randomly. The distraction and neutral digit strings are matched for difficulty level and reliability to avoid problems associated with differential discrimination power (Reference Chapman and ChapmanChapman & Chapman, 1978). The total number of correctly recalled digits for the neutral and distractor lists is divided by a maximum score for comparison between conditions. The score (percentage of correctly recalled digits) for each condition is used in the analysis.

Continuous Performance Test, Identical Pairs version (CPT—IP)

The CPT—IP is a multi-dimensional CPT task that systematically varies type of stimulus, distraction and stimulus exposure time (Reference Cornblatt, Lenzenweger and Erlenmeyer-KimlingCornblatt et al, 1989). Four stimuli conditions are used: numbers; shapes; numbers presented with distractors; and shapes presented with distractors. The test consists of both a slow and a fast condition for each of the four conditions. Computer-generated stimuli are presented on a monitor. The subject is asked to respond as fast as possible by lifting the index finger from a reaction time key whenever two identical stimuli follow each other. For each condition, a series of 150 trials are continually flashed on the screen, with stimulus onset time of 50 ms and dark interval between stimuli of 950 ms.

A subset of measures were selected from each test to be entered as input variables in an overall ‘second-generation’ principal component analysis. The selection of measures from each test was based on a combination of the theoretical foundation of the essential quality of the test, clinical experience and principal component analysis. For example, for the CPT a factor analysis indicated that the best solution was to use the average of hits, false alarms and reaction time across all conditions.

RESULTS

Table 2 gives the mean scores for the selected subset of variables. Compared with standard norms presented in the test manuals and available literature for the DSDT (Reference RundRund, 1983) and BMT (Reference Rund, Øie and SundetRund et al, 1996), the sample's mean scores indicated a function clearly below normal for most of the tests. A prominent exception was the WCST, where most of the patients scored close to normal.

Table 2

The variables selected for the final factor analysis

Mean s.d. Range
California Verbal Learning Test (CVLT)
Immediate recall (sum total for the five learning attempts) 53.7 11.4 17.0-77.0
Delayed free recall 12.0 3.0 4.0-16.0
Errors (mean scores for category cued recall, retest, delayed free recall and delayed category cued recall) 0.5 0.7 0.0-4.5
Perseverative responses (mean score for the five attempts) 0.8 0.7 0.0-3.4
Backward Masking Test (BMT)
Mean score for 49 and 33 ms 6.7 4.5 0.0-18.5
Finger Tapping Test (FTT)
Mean score for dominant and non-dominant hand 48.1 8.6 23.0-73.1
Wisconsin Card Sorting Test (WCST)
Categories completed 5.2 1.4 0.0-6.0
Perseverations 16.4 12.1 2.0-73.0
Number of attempts to first category 19.8 19.8 10.0-129.0
Failure to maintain sets 0.9 1.2 0.0-6.0
Controlled Oral Word Association task (COWA):
Sum of F-words, A-words and S-words 32.0 10.8 8.0-63.0
Trail Making Test (TMT)
Time for completing part B 86.3 45.3 22.8-300.0
Digit Span Distractibility Test (DSDT)
Digit span without distractor 78.1 18.2 0.0-100.0
Digit span with distractor 75.4 20.5 0.0-100.0
Continuous Performance Test, Identical Pairs version (CPT—IP)
Hits (the mean ratio of all six conditions) 0.57 0.20 0.02-0.98
False alarms (the mean ratio of all six conditions) 0.26 0.15 0.00-0.71
Reaction time (the mean score of all six conditions) 542.8 60.7 368.0-710.0

The intercorrelations between the 17 variables are given in Table 3. As seen from this table, all four WCST variables were strongly to moderately intercorrelated, and so were the CVLT scores except for perseverations. TMT, COWA, DSDT and CPT hits were also strongly to moderately intercorrelated. CPT false alarms and CPT reaction time were moderately intercorrelated, whereas FTT was basically uncorrelated with all the other variables.

Table 3

Intercorrelations between the 17 variables

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17
1. CVLT Immediate recall xx 0.80 -0.30 0.24 -0.24 -0.25 0.32 -0.28 0.32 0.31 0.26
2. CVLT Delayed free recall xx -0.35 0.26 -0.26 -0.25 0.32 -0.29 0.24 0.27 0.26
3. CVLT Errors xx
4. CVLT Perseverations xx
5. BMT xx 0.21 -0.23 0.35
6. FTT xx 0.22 -0.21
7. WCST Categories completed xx -0.71 -0.69 -0.41 -0.22 0.26 0.26 0.27
8. WCST Perseverative responses xx 0.43 0.25 -0.21 0.25 -0.26 -0.28 -0.34
9. WCST Number of attempts xx 0.29 0.26
10. WCST Failure to maintain set xx
11. COWA xx -0.37 0.26 0.31 0.43
12. TMT xx -0.32 -0.27 -0.45
13. Digit span without distractor xx -0.66 -0.35
14. Digit span with distractor xx 0.44
15. CPT Hits xx 0.22
16. CPT False alarms xx -0.37
17. CPT Reaction time xx

The 17 tests were included in a factor (principal component) analysis with varimax rotation. We wanted to be sure that the factor solution could account for a considerable proportion of the variance of the included variables. We therefore chose to exclude variables with communalities <0.50. The first analysis gave six factors with eigenvalue >1. Two variables (CVLT perseverations and WCST failure to maintain sets) had communalities <0.50. We reran the analysis with the 15 remaining variables and found five factors with eigen-value >1. From this factor solution two more variables (BMT and TMT) had to be excluded because of communality <0.50. We finally ended with 13 variables, for which the factor analysis again gave five factors with eigenvalue >1. Together, the five factors explained nearly 72% of the variance. The communalities and the factor loadings are given in Table 4.

Table 4

Communalities and the factor loadings of the 13 final variables

Communalities F1 F2 F3 F4 F5
1. CVLT Immediate recall 0.79 0.81
2. CVLT Delayed free recall 0.82 0.85
3. CVLT Errors 0.50 -0.68
6. FTT 0.81 -0.87
7. WCST Categories completed 0.88 0.92
8. WCST Perseverative responses 0.69 -0.78
9. WCST Number of attempts, one category 0.70 -0.82
11. COWA 0.58 0.56 0.43
13. Digit span without distractor 0.71 0.79
14. Digit span with distractor 0.70 0.81
15. CPT Hits 0.66 0.65 0.42
16. CPT False alarms 0.72 0.76 0.32
17. CPT Reaction time 0.76 -0.82

Based on the factor analysis we chose to make an index score for each of the five dimensions. A variable was included in an index if:

  1. (a) it had a strong loading (≥0.50) on the corresponding factor;

  2. (b) the strong loading was specific for this factor (the difference between the loading on the corresponding factor and the highest loading on a non-corresponding factor had to be >0.10).

We z-transformed the variables and calculated the mean of the items of each index (with negative sign if items were reversed).

This gave us the following five index scores:

  1. (a) Working memory (four items: COWA, Digit span with and without distractor and CPT hits).

  2. (b) Executive function (three items, all from the WCST: categories completed, perseverative responses (reversed), number of attempts to first category (reversed)).

  3. (c) Verbal learning (three items, all from the CVLT: immediate recall, delayed free recall, errors (reversed)).

  4. (d) Impulsivity (two items, both from the CPT: false alarms and reaction time (reversed)).

  5. (e) Motor speed (one item only: finger-tapping).

For the first four indices the internal consistency could be calculated. It had a median of 0.73 (range: 0.54 (impulsivity) to 0.82 (executive function)).

The correlations between the index scores and the factor scores had a median of 0.95 (range 0.87 to 0.98), indicating that the index scores could replace the factor scores without substantial loss of information.

The intercorrelations between the index scores are shown in Table 5. As seen from the table, the five scores seemed to represent fairly independent dimensions.

Table 5

Intercorrelations between the five dimensions

WM EF VL Im MS
Working memory (WM) xx 0.33 0.37 0.02 0.09
Executive function (EF) xx 0.31 0.01 0.23
Verbal learning (VL) xx -0.16 0.02
Impulsivity (Im) xx -0.01
Motor speed (MS) xx

We also looked at the relationship between the dimension scores and age, gender, education, diagnosis and GAF symptom and function scores. Because of multiple comparisons and the fairly high number of patients, we chose a significance level of 0.001. No dimensions were significantly correlated with age. The difference between genders was clearly significant for motor speed (P <0.0005), with women having lower scores. Years of education were significantly correlated with working memory (=0.29, P<0.005) and verbal learning (r=0.30, P<0.0005).

We did not find any significant relations between any of the neurocognitive dimensions and core/non-core diagnosis, GAF symptom or GAF function scores.

DISCUSSION

How many dimensions?

This study has identified five distinct dimensions that seem clinically meaningful and psychometrically sound. The five dimensions comprise information from six of the eight tests. Data from two of the tests, BMT and TMT, did not meet our criteria for inclusion and seem to assess neurocognitive dimensions of uncertain validity, at least in this sample. Four of the index scores (executive function, verbal learning, impulsivity and motor speed) include sub-tests from one test only. Working memory is more complex, as it comprises quite different tests as COWA, Digit span (with and without distraction) and CPT hits. Our working memory index is a composite measure, combining verbal fluency, immediate memory and vigilance. The inclusion of CPT hits is not surprising as successful completion of the vigilance tasks clearly depends on immediate memory. However, the vigilance tasks involve more than what Perry et al (Reference Perry, Heaton and Potterat2001) call ‘transient online and retrieval’ working memory. They demand ability to store, manipulate and retrieve data, and to keep attention over time. The study of Conklin et al (Reference Conklin, Curtis and Katsanis2000) also indicates that forward and backward digit span tasks tap different cognitive abilities. Our working memory index seems to be most strongly related to immediate memory, probably indicating that in the present sample the variability of immediate memory was so large that it gave no room for an additional factor covering the more specific aspects of vigilance. A partly alternative explanation would be in line with the suggestion by Perry et al (Reference Perry, Heaton and Potterat2001) that patients with psychosis may have more general deficits that will influence both working memory and vigilance. In this connection it is worth noting that executive function came out as a separate dimension, which may indicate that the WCST taps a different underlying brain substrate. Such an interpretation is further supported by the fact that even if most of the patients performed clearly poorer than normals on most tests, the majority performed rather well on the WCST.

Can the CPT measure impulsivity?

The impulsivity sub-scale is a new construction. In the present sample there was a clear inverse relationship between the CPT false alarm and the CPT reaction time, and when combined they seemed to give a measure of impulsivity. However, the relationship between the two variables could prove to be a more complex one, as a comparison with normals seemed to indicate that the patients had both a higher percentage of false alarms and a longer reaction time.

Relationship with other variables

Our second main finding was that the dimension scores were weakly related to factors such as education, gender, age, diagnosis and symptom level. We cannot rule out the possibility that more specific findings may be obtained in future analyses of our data, when we go into details of the specific neurocognitive tests and look at diagnostic subgroups and variables such as DUP. By contrast, the five dimensions explained most of the variance in our data-set, and the fact that the group as a whole scored below average on most of the dimensions might imply that the level of neurocognitive functioning is compromised even in a basically remitted sample of patients with first-episode psychosis. If this finding is replicated in our total sample, it could indicate that neurocognitive deficiencies are vulnerability factors for psychosis, more than a result of the psychotic process. However, it might be that neurocognitive function can improve over time, but that such an improvement takes a longer time than symptomatic remission. Only a follow-up investigation can tell us whether this is the case or not. Such a study is under way as part of the Tidlig Intervensjon ved Psykoser (TIPS: Early Intervention in Psychosis) project.

Limitations

Even if this study is based on a considerable number of patients, the results have to be regarded as preliminary. Replicatory studies are needed to demonstrate the robustness of the identified dimensions.

CLINICAL IMPLICATIONS

  1. ▪ Working memory, verbal learning and executive function are fairly weakly intercorrelated.

  2. ▪ Even in a first-episode sample, many patients function poorly on one or more neurocognitive tests.

  3. ▪ Neurocognitive test scores seem to be weakly related to education, gender, age, diagnosis and symptom level.

LIMITATIONS

  1. ▪ Several patients were tested more than 3 months after admission (some of them much later).

  2. ▪ A considerable number of patients were lost to neurocognitive testing.

  3. ▪ The paper is based on cross-sectional data only.

Acknowledgements

The authors thank the following for help with the collection of neurocognitive data: Julie Bjørnsen, Nils Johan Halleråker, Patricia Jansen, Per Knudsen, Liv Jæger Midbøe, Olaug Moi, Jan Mydland, Gerd Berit Mygland, Susanne Theill Møller, Lillian Møllerhaug, Caroline Ripa, Patricia Schultz, Kjersti Tvedt, Erik Tveterås, Torill Ueland, Wenche ten Velden, Mette Væver and Eystein Våpenstad. We also thank Jan Egil Norvik for invaluable help with structuring the database of the project.

Footnotes

∗

Presented in part at the European First Episode Schizophrenia Network Meeting, Whistler BC, Canada, 27 April, 2001.

This paper is part of the Tidlig Intervensjon ved Psykoser (TIPS: Early Intervention in Psychosis) project with the following research group: T.H.M.; PV.; S.F.; Ulrik Haahr; Jan Olav Johannessen; Tor Ketil Larsen; Ingrid Melle; Stein Opjordsmoen; Bj⊘rn Rishovd Rund; and Erik Simonsen.

Declaration of interest

The study was supported by the Norwegian Research Council and by NIMH 01654 (T.H.M.).

This paper is part of the Tidlig Intervensjon ved Psykoser (TIPS: Early Intervention in Psychosis) project with the following research group: T.H.M.; P.V.; S.F.; Ulrik Haahr; Jan Olav Johannessen; Tor Ketil Larsen; Ingrid Melle; Stein Opjordsmoen; Bjørn Rishovd Rund; and Erik Simonsen.

References

American Psychiatric Association (1994) Diagnostic and Statistical Manual of Mental Disorders (4th edn) (DSM–IV). Washington, DC: APA.Google Scholar
Bechtoldt, H. P., Benton, A. L. & Fogel, M. L. (1962) An application of factor analysis in neuropsychology. Psychological Record, 12, 147–156.CrossRefGoogle Scholar
Bell, M. D., Conway, T. C., Kaplan, E., et al (1997) Wisconsin Card Sorting Test dimensions in schizophrenia: Factorial, predictive, and divergent validity. Journal of Clinical and Experimental Neuropsychology, 19, 933–941.Google Scholar
Bilder, R. M., Goldman, R. S., Robinson, D., et al (2000) Neuropsychology of first-episode schizophrenia: Initial characterization and clinical correlates. American Journal of Psychiatry, 157, 549–559.CrossRefGoogle ScholarPubMed
Chapman, L. J. & Chapman, J. P. (1978) The measurement of differential deficits. Journal of Psychiatric Research, 14, 303–311.Google Scholar
Conklin, H. M., Curtis, C. E., Katsanis, J., et al (2000) Verbal working memory impairment in schizophrenia patients and their first-degree relatives: evidence from the Digit Span Task. American Journal of Psychiatry, 157, 275–277.Google Scholar
Cornblatt, B. A., Lenzenweger, M. F. & Erlenmeyer-Kimling, M. (1989) The Continuous Performance Test, Identical Pairs version. II: Contrasting attentional profiles in schizophrenic and depressed patients. Psychiatry Research, 29, 65–85.CrossRefGoogle ScholarPubMed
Delis, D. C., Kramer, J. H., Kaplan, E., et al (1987) The California Verbal Learning Test (CVLT): Manual. New York: The Psychological Corporation.Google Scholar
Delis, D. C., Freeland, J., Kramer, J. H., et al (1988) Integrating clinical assessment with cognitive neuroscience: Construct validation of the California Verbal Learning Test. Journal of Consulting and Clinical Psychology, 56, 123–130.CrossRefGoogle ScholarPubMed
Green, M. F. (1998) Schizophrenia from a Neurocognitive Perspective. Probing the Impenetrable Darkness. Boston, MA: Allyn and Bacon.Google Scholar
Green, M. F. Neuchterlein, K. & Mintz, J. (1994a) Backward masking in schizophrenia and mania. I: Specifying a mechanism. Archives of General Psychiatry, 51, 934–944.Google Scholar
Green, M. F. Neuchterlein, K. & Mintz, J. (1994b) Backward masking in schizophrenia and mania. II: Specifying visual channels. Archives of General Psychiatry, 51, 945–951.Google Scholar
Heaton, R. K., Chelune, G. J., Talley, J. L., et al (1993) Wisconsin Card Sorting Test. Manual. Revised and Expanded. Odessa, FL: Psychological Resources.Google Scholar
Heaton, R. K., Grant, I., Butters, N., et al (1995) The HNRC 500–neuropsychology of HIV infection at different disease stages. Journal of the International Neuropsychological Society, 1, 231–251.Google Scholar
Johannessen, J. O., McGlashan, T. H., Larsen, T. K., et al (2001) Early detection strategies for untreated first-episode psychosis. Schizophrenia Research, 51, 39–46.CrossRefGoogle ScholarPubMed
Kareken, D. A., Moberg, P. J. & Gur, R. D. (1996) Proactive inhibition and semantic organization: Relationship with verbal memory inpatients with schizophrenia. Journal of the International Neuropsychological Society, 2, 486–493.Google Scholar
Koren, D., Seidman, L. J., Harrison, R. H., et al (1998) Factor structure of the Wisconsin Card Sorting Test: Dimension of deficit in schizophrenia. Neuropsychology, 12, 289–302.Google Scholar
Larsen, T. K., McGlashan, T. H., Johannessen, J. O., et al (2001) Shortened duration of untreated first episode of psychosis: changes in patient characteristics at treatment. American Journal of Psychiatry, 158, 1917–1919.CrossRefGoogle ScholarPubMed
Laws, K. R. (1999) A meta-analytic review of Wisconsin Card Sort studies in schizophrenia: General intellectual deficit in disguise? Cognitive Neuropsychiatry, 4, 1–35.CrossRefGoogle ScholarPubMed
Lezak, M. D. (1995) Neuropsychological Assessment (3rd edn). New York: Oxford University Press.Google Scholar
Lieh-Make, F. & Lee, R. W. H. (1997) Cognitive deficit measures in schizophrenia: Factor structure and clinical correlates. American Journal of Psychiatry, 154, 39–46.Google Scholar
Oltmanns, P. F. & Neale, J. N. (1975) Schizophrenic performance when distractors are present: attention deficit or differential task difficulty? Journal of Abnormal Psychology, 84, 205–209.Google Scholar
Perry, W., Heaton, R. K., Potterat, E., et al (2001) Working memory in schizophrenia: Transient online storage versus executive functioning. Schizophrenia Bulletin, 27, 157–176.CrossRefGoogle ScholarPubMed
Rund, B. R. (1983) The effect of distraction on focal attention in paranoid and non-paranoid schizophrenic patients compared to normals and non-psychotic psychiatric patients. Journal of Psychiatric Research, 17, 241–250.Google Scholar
Rund, B. R. (1993) Backward-masking performance in chronic and non-chronic schizophrenics, affectively disturbed patients, and normal control subjects. Journal of Abnormal Psychology, 102, 74–81.CrossRefGoogle Scholar
Rund, B. R. & Borg, N. E. (1999) Cognitive deficits and cognitive training in schizophrenic patients: a review. Acta Psychiatrica Scandinavica, 100, 85–95.Google Scholar
Rund, B. R., Øie, M. & Sundet, K. (1996) Backward masking deficit in adolescents with schizophrenic disorders or attention deficit hyperactivity disorder. American Journal of Psychiatry, 153, 1154–1157.Google Scholar
Spaulding, W., Hargrove, S., Crinean, W., et al (1981) Microcomputer-based laboratory for psychopathology research in rural settings. Behaviour Research Methods and Instrumentations, 13, 616–623.CrossRefGoogle Scholar
Spreen, O. & Benton, A. L. (1969) Neurosensory Center Comprehensive Examination for Aphasia. Manual and Instructions (NCCEA). Victoria, BC: University of Victoria.Google Scholar
Spreen, O. & Strauss, E. (1998) A Compendium of Neuropsychological Tests: Administration, Norms, and Commentary (2nd edn). New York: Oxford University Press.Google Scholar
Vanderploeg, R. D., Schinka, J. A. & Retzlaff, P. (1994) Relationships between measures of auditory verbal learning and executive functioning. Journal of Clinical Experimental Neuropsychology, 16, 243–252.CrossRefGoogle ScholarPubMed
Wiegner, S. & Donders, J. (1999) Performance on the Wisconsin Card Sorting Test after traumatic brain injury. Assessment, 6, 179–187.Google Scholar
Figure 0

Table 1Demographic variables and symptom scores

Figure 1

Table 2The variables selected for the final factor analysis

Figure 2

Table 3Intercorrelations between the 17 variables

Figure 3

Table 4Communalities and the factor loadings of the 13 final variables

Figure 4

Table 5Intercorrelations between the five dimensions

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