Archives of Clinical Neuropsychology 29 (2014) 60–74

Spanish Multicenter Normative Studies (NEURONORMA Project): Normative Data and Equivalence of Four BNT Short-Form Versions

1

Behavioral Neurology Group, Institut Hospital del Mar d’Investigacions Me´diques, Barcelona, Spain 2 Universitat Autuˆ˙noma de Barcelona, Spain 3 Service of Geriatrics, Internal Medicine, Hospital Universitario Dr. Jose´ E. Gonzalez, Monterrey, Me´xico 4 Section of Behavioral Neurology and Dementias, Hospital del Mar, Barcelona, Spain 5 Service of Neurology, Hospital Mu´tua de Terrassa, Terrassa, Spain 6 Service of Neurology, Hospital Clı´nic, Barcelona, Spain 7 Service of Neurology, Hospital Clı´nico Universitario, Santiago de Compostela, Spain 8 Service of Neurology, Hospital Clı´nico San Carlos, Madrid, Spain 9 Service of Neurology, Hospital Virgen Arrixaca, Murcia, Spain 10 Service of Neurology, Hospital Virgen Macarena, Sevilla, Spain 11 Department of Neurology, Hospital Universitario La Paz, Madrid, Spain 12 Service of Neurology, Hospital de Cruces, Bilbao, Spain 13 Service of Neurology, Hospital de la Santa Creu i Sant Pau, Barcelona, Spain *Corresponding author at: Section of Behavioral Neurology and Dementias, Hospital del Mar, IMIM, Biomedical Research Park Building, Carrer Dr. Aiguader, 88, 08003 Barcelona, Spain. Tel.: +34-933160778; fax: +34-933160723. E-mail address: [email protected] (J. Pen˜a-Casanova). Accepted 9 October 2013

Abstract The application of the Boston Naming Test (BNT) is time-consuming and shortened versions need to be developed for screening purposes. The aims of this study were to develop four equivalent 15-item forms of a Spanish adaptation of the BNT, to test the equivalence of the new versions in a clinical sample, and to provide normative data. The normative sample consisted of 340 subjects. The clinical sample included 172 patients (76 Mild Cognitive Impairment and 96 Alzheimer’s disease). An empirical procedure was used to develop the shortened versions. All new versions demonstrated satisfactory internal consistency. Pearson’s coefficient analysis showed strong relationships among the four shortform versions as well as between each of them and the 60-item test. The inferential confidence interval method demonstrated the equivalence between the four shortened versions. Age and education affected the score of all short-form versions, but sex was found to be unrelated to the performance. Normative data were calculated for midpoint age groups. This paper proposes four 15-item equivalent versions that could be useful and time-saving tools for screening purposes. Keywords: Boston Naming Test; Short forms; Equivalence; Normative data

Introduction Word retrieval difficulty is one of the most prevalent symptoms associated with neuropsychological impairment. Anomia has been related to many neurological disorders such as dementia, left temporal lobe epilepsy, or cerebrovascular events. The Boston Naming Test (BNT; Kaplan, Goodglass, & Weintraub, 1978) is one of the most commonly used tests for the assessment of confrontation naming (Rabin, Barr, & Burton, 2005). Several reports have shown that the BNT efficiently discriminates the healthy # The Author 2013. Published by Oxford University Press. All rights reserved. For permissions, please e-mail: [email protected]. doi:10.1093/arclin/act085 Advance Access publication on 11 November 2013

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Marta Casals-Coll1,2, Gonzalo Sa´nchez-Benavides 1, Sandra Meza-Cavazos 1,3, Rosa M. Manero4, Miguel Aguilar5, Dolors Badenes5, Jose´ Luis Molinuevo6, Alfredo Robles7, Marı´a Sagrario Barquero8, Carmen Antu´nez9, Carlos Martı´nez-Parra 10, Anna Frank-Garcı´a 11, Manuel Ferna´ndez12, Rafael Blesa13, Jordi Pen˜a-Casanova1,3,*, for the NEURONORMA Study Team

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elderly from those with dementia (LaBarge, Edwards, & Knesevich, 1986; Lansing, Ivnik, Cullum, & Randolph, 1999; Martin & Fedio, 1983; Welch, Doineau, Johnson, & King, 1996). A first experimental version of the BNT included 85 items (Kaplan et al., 1978). The modified version, published in 1983, was limited to 60 drawings (Kaplan, Goodglass, & Weintraub, 1983). In 2001, Kaplan, Goodglass, and Weintraub published the second edition of the test, with multiple-choice options and error codes to categorize incorrect responses, which included a 15-item shortform developed by Mack, Freed, Williams, and Henderson (1992). There is a large volume of published normative studies concerning the BNT in various languages (see Lezak, Howieson, & Loring, 2004; Mistrushina, Boone, Razani, & D’Elia, 2005; Strauss, Sherman, & Spreen, 2006; for a review). The contribution of the MOANS and MOAANS projects to this test has been considerable providing normative data for elder Americans and Afro-Americans subjects (Lucas et al., 2005; Steinberg, Bieliauskas, Smith, Langellotti, & Ivnik, 2005). Zec, Burkett, Markwell, and Larsen (2007) also provided normative data from a sample of 1026 subjects aged over 49 years. There are a number of versions of the BNT in Spanish. A first 60-item version was proposed as an adaptation to Spanish from the modified version (Kaplan, Goodglass, & Weintraub, 1986). A second modified version was proposed as a new adaptation for Spanish speaking populations (Kaplan, Goodglass, & Weintraub, 2005). Previous studies have presented normative data in Spanish, one from an Argentinean sample (Allegri et al., 1997), others from a young adult Spanish sample (Aranciva et al., 2012; Quin˜ones-Ubeda, Pen˜a-Casanova, Bo¨hm, Gramunt-Fombuena, & Comas, 2004). Recently, two studies have published normative data from a sample of elderly Spanish subjects (Pen˜a-Casanova, Quin˜ones-Ubeda, et al., 2009; Rami et al., 2008). Various short-form versions of BNT have been proposed. They could offer many advantages in clinical assessment, especially when impaired or low educational level patients are examined (e.g., short forms may be less taxing for low educational level patients). Short-form versions are also essential in the test– retest designs in treatment monitoring or in research studies (Calero, Arnedo, Navarro, Ruiz-Pedrosa, & Carnero, 2002; Fastenau, Denburg, & Mauer, 1998; Mack et al., 1992). The administration of the 60-item version of the BNT requires 15– 30 min, time that is beyond the scope of a routine screening for cognitive impairment (Deveugele, Derese, van den Brink-Muinene, Bensing, & De Maeseneer, 2002; Villarejo & Puertas-Martı´n, 2011). In order to improve the efficiency of the assessment, shorter versions of the BNT have been developed. A variety of methods was used to construct abbreviated versions. Specifically, for the 30-item versions, an even and an odd version were developed from the 60-item test (Williams, Mack, & Henderson, 1989). The same authors built an empirical version by examining differences between group means of individual items from normal controls and patients with Alzheimer disease (Williams et al., 1989). These two versions have been analyzed by a large number of authors (Fisher, Tierney, Snow, & Szalai, 1999; Graves, Bezeau, Fogarty, & Blair, 2004; Jefferson et al., 2007; Kent & Luszcz, 2002; Lansing et al., 1999; Mack et al., 1992; Tombaugh & Hubley, 1997). Fastenau and colleagues (1998) combined the four 15-item versions developed by Mack and colleagues (1992) to construct two 30-item versions. Saxton and colleagues (2000) created two empirical versions on the basis of achieving equivalent word frequency. Using item response theory, Graves and colleagues (2004) developed another 30-item version treating the difficulty of each item as information to be incorporated in the selection of items. Regarding 15-item versions, the first proposal was suggested in 1989 by the Consortium to Establish a Registry for Alzheimer’s disease (CERAD). This version was later assessed by several authors (Kent & Luszcz, 2002; Lansing et al., 1999; Mack et al., 1992). In addition, Teng and colleagues (1989) developed four 15-item versions by using item redistribution according to its difficulty. Afterwards, Mack and colleagues (1992) published four 15-item versions in order to establish equivalence among them. An empirical version was created on the basis of the item discrimination capacity between normal controls and Alzheimer’s disease patients (Lansing et al., 1999). Graves and colleagues (2004) made a 15-item version using the same methodology as in their 30-item version. Although a considerable amount of shortened versions of the test have been developed for diverse populations, most of the authors conclude that a reliable shortened version should be specially designed and validated for each target population. As all these shortened versions of BNT were devised for English-speaking communities, several items were not appropriate for populations with a different cultural background. On these grounds, Serrano and colleagues (2001) developed a 12-item shortened version adapted to Argentina. Later, Calero and colleagues (2002) tested the shortened version proposed by Mack and colleagues (1992) in southern Spain. Recently, Nebreda and colleagues (2011) proposed a short-form version for language screening in dementia in a bilingual rural community in Galicia (Ferna´ndez-Bla´zquez et al., 2012). The present report is part of the NEURONORMA project, a multicenter study of normalization and validation of neurocognitive and functional tools with genetic and neuroimaging correlation for the detection, diagnosis, and follow-up of cognitive deterioration in aging and dementia (Pen˜a-Casanova, Blesa, et al., 2009), which represents the most comprehensive and largest normative study for a Spanish population on selected neuropsychological tests. This project was designed following a specific methodology allowing the co-normalization of a battery of tests covering different cognitive areas. Accordingly, the hypothesis we tested in this study was that four 15-item specially designed shortened versions of the BNT could be used equally in a dementia screening context. The aims of the study were therefore: (a) to design four shortened versions as an alternative to the 60-item BNT; (b) to study equivalence among each other; and (c) to provide normative data for the four short versions from a Spanish adult control sample.

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Materials and Methods Research Participants

Cognitively normal adult definition. Entry criteria for the control group included consecutive individuals according to a series of inclusion and exclusion criteria. Recruitment procedures and socio-demographic characteristics of the sample have been reported in a previous paper (Pen˜a-Casanova, Blesa, et al., 2009). Volunteers did not need to be completely medically healthy to participate (Pedraza et al., 2005). Patients with active, chronic medical, psychiatric, or neurological conditions or physical disabilities or handicaps were included if the researcher judged that the condition was correctly controlled or resolved and not causing cognitive impairment. The same criterion was applied in the case of use of psychoactive medications. Three hundred and forty subjects were included in the BNT control sample (Pen˜a-Casanova, Quin˜ones-Ubeda, et al., 2009), 202 women and 138 men, between 50 and 85 years old, with a mean age of 65 years (SD ¼ 9.3) and a mean education of 10.5 years (SD ¼ 5.5). The BNT normative sample demographic information is presented in Table 1. The clinical sample definition. All patients were recruited from dementia consultations at nine hospitals from different regions of Spain (see Pen˜a-Casanova, Blesa, et al., 2009 for details). As part of the recruitment protocol subjects were interviewed by skilled clinicians to explore relevant medical antecedents and the presence of depressive symptoms, functional disability, and cerebrovascular risk. For such purpose, the Hamilton Depression Rating Scale (Hamilton, 1960), the IDDD, and the Modified Ischemia Score (Rosen, Terry, Fuld, Katzman, & Peck, 1980) were administered. The current sample was composed of patients with cognitive impairment who came from the NEURONORMA project (Quintana et al., 2011) and to whom the BNT was administered. One hundred and seventy-two subjects were included in the Table 1. Normative sample sociodemographic characteristics

Sex Men Women Groups of age (years) 50–56 57–59 60–62 63–65 66–68 69–71 72–74 75–77 78–80 .80 Education (years) 0 –5 6 –12 .12

Count

Percent of total

138 202

40.6 59.4

75 51 33 18 25 49 31 29 19 10

22.0 15.0 9.7 5.3 7.3 14.4 9.1 8.5 5.6 2.9

69 151 120

20.3 44.4 35.3

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A total sample of 535 subjects was included in the entire NEURONORMA project. Participants included 356 cognitively normal adults, 79 patients diagnosed with Mild Cognitive Impairment (MCI), and 100 patients diagnosed with AD. The ethnic background of all participants was Caucasian. The project was reviewed and approved by the Research Ethics Committee of the Municipal Institute of Medical Care of Barcelona, Spain, and was conducted in accordance with the Declaration of Helsinki (World Medical Association, 1977) and its subsequent amendments, and the European Union regulations concerning medical research. All participants were required to have an informant who could answer questions about their cognition, function, and health. The diagnosis, included the selection of controls, was based on a clinical interview with the patient and the informant and physical and neurological examination. An initial cognitive assessment was completed by trained neuropsychologists. The selection tests were the Mini-Mental State Examination (Folstein, Folstein, & McHugh, 1975) in a validated Spanish version (Blesa et al., 2001), the abbreviated Barcelona Test (Pen˜a-Casanova, 2005; Quintana et al., 2011, 2012), and the Interview for Deterioration of Daily Living in Dementia (IDDD; Teunisse, Derix, & Crever, 1991) in its validated Spanish version (Bo¨hm et al., 1998) was used to evaluate functional status.

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BNT clinical sample, 105 women and 67 men, with a mean age of 73 years (SD ¼ 7.13) and a mean education of 7.83 years (SD ¼ 4.78). Seventy-six patients were diagnosed with amnestic MCI according the following criteria: (a) presence of subjective memory complaints; (b) functional abilities essentially preserved confirmed by an informant; (c) a minimal evolution of 6 months; (d) evidence of objective memory impairment, defined as a score below the 15th percentile of the age and education-matched control group on a test of verbal delayed recall (Barcelona Test paragraph recall), but no other significant deficits on neuropsychological examination; (e) National Institute of Neurological and Communication Disorders and Stroke-Alzheimer’s Disease and Related Disorders Association (NINCDS-ADRDA; McKhann et al., 1984) criteria for probable AD not met; and (f) a Global Deterioration Scale (GDS; Reisberg, Ferris, de Leon, & Crook, 1982) score of 3. Ninety-six patients with a diagnosis of probable Alzheimer disease fulfilled Diagnostic and Statistical Manual for the Mental Disorders-Fourth Edition criteria (DSM-IV; American Psychiatric Association, 1994) and NINCDS-ADRDA criteria; they were at mild to moderate dementia stages and were at GDS stages 4 and 5.

The neuropsychological tests of the entire project were administered as part of the NEURONORMA battery (Pen˜a-Casanova, Blesa, et al., 2009). Although other measures were included as part of this larger study, the authors chose only to investigate the BNT for the purpose of this paper. Tests were administered and scored by neuropsychologists specifically trained for this project. The test consists of a book with 60 cards with black and white drawings to be named. On the back of each card there are four printed name choices (semantically, phonologically, or perceptively related to the word target). Following the BNT instructions, participants were allowed up to 20 s to name each item. A stimulus cue was provided when no response was given after 20 s, the participant stated that he/she did not know the name, or the item was incorrectly perceived. First, he/she was given the semantic stimulus cue and again allowed up to 20 s to name the picture. If the participant still did not recognize the picture after receiving the semantic cue, or misnamed the picture, the examiner proceeded to phonemic cueing. In those cases in which the participant named the semantic class, or superordinate, he/she was prompted to give the specific name. Finally, after the test was completed, the examiner returned to each item incorrectly named after a phonemic cue and presented the card with that item and the four printed name choices. The examiner read each word and asked the participant to indicate the correct name. The total score was the number of correct responses produced spontaneously and with the aid of semantic cue. Maximum score was 60 for the 60-item version and 15 for the four shortened versions that were developed specifically for this study. ´ beda et al., 2004) of the latest BNT version (Kaplan et al., 2001) was applied in A Spanish experimental adaptation (Quin˜ones-U this study. This latest BNT version was slightly modified in order to adapt the test to Spain. The process of adaptation was described ´ beda et al., 2004). Briefly, the procedure was the in previous papers (Pen˜a-Casanova, Quin˜ones-Ubeda, et al., 2009; Quin˜ones-U following: A multiple choice form was developed following a three-step process. First, three translations into Spanish were prepared by researchers. Second, the three translations were reconciled into one version, and words checked in the official dictionary of the Royal Academy of Spanish Language (2001). Finally, this version was tested empirically for clarity and acceptability of wording with four individuals who were native in Spanish. In order to adapt the vocabulary to Spain, an extra item was added: “magdalena” (a cupcake or fairy cake made in a small paper cup container [muffin]), as an alternative to “pretzel.” Standard instructions indicate beginning with Item 30 and proceeding forward unless an error is made prior to achieving eight consecutive correct responses. Instead of standard instructions, as this was a normative study, the test was administered entirely from Item 1 to Item 60 to know the specific contribution of each item on the final score. Data Management and Statistical Analyses With the purpose of developing four 15-item short versions (A, B, C, and D), BNT items were arranged by correct answer percentage in decreasing order. An item named spontaneously or after being provided with the semantic cue was considered a correct answer. Subsequently, an item balanced assignment to short forms was completed (Table 2). It was performed by carrying out the following sequence: A, B, C, D – D, A, B, C – C, D, A, B – B, C, D, A, and so on, to balance difficulty among the four versions (Table 3). Basic descriptive analyses included mean and standard deviation. In order to obtain a measure of internal consistency, Cronbach’s alpha was calculated. Following the suggestion of a reviewer and the indications of Ross, Furr, Carter, and Weinberg (2006), this study employed Tryon’s (2001) method for examining statistical equivalence between all shortened versions using inferential confidence intervals (CIs) as an adjunct to null hypothesis significance testing (NHST). This first method compares the maximum probable difference between two means, also called Rg, to delta, a value that represents an amount considered inconsequential. Rg is the range of two appropriately reduced inferential CIs. Rg begins with the lower CI limit of the lesser mean and extends to the upper CI limit of the greater mean. If Rg is less than delta, then the maximum amount of difference between test forms can be considered

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Neuropsychological Measures

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Table 2. Correct answer percentage from the results in the normative sample (n ¼ 340) and item assignment to A, B, C, and D short-form versions Item

Word

Version

100.000 100.000 100.000 100.000 100.000 100.000 99.709 99.709 99.709 99.128 99.128 98.837 98.837 98.547 98.256 97.965 97.965 97.674 97.384 97.384 97.093 96.802 96.802 96.221 95.349 95.058 94.477 92.733 92.442 91.860 90.698 90.116 88.372 85.756 84.302 84.302 83.721 81.977 80.523 79.942 72.384 69.477 66.279 65.988 62.791 62.500 62.500 61.337 59.012 58.721 57.558 55.233 53.779 52.035 47.965 30.523 26.744 19.767 14.826 6.977 6.686

1 2 4 6 7 12 8 10 22 9 20 5 37 16 17 13 14 15 3 46 21 11 44 18 47 49 28 23 32 43 35 54 50 36 30 31 24 61 38 27 52 39 40 25 48 53 58 26 41 34 56 51 33 45 55 42 60 29 59 57 19

Cama (bed) ´ rbol (tree) A Casa (house) Tijeras (scissors) Peine (comb) Escoba (broom) Flor (flower) Cepillo de dientes (toothbrush) Caracol (snail) Sierra (saw) Banco (bench) Silbato (whistle) Escaleras meca´nicas (escalator) Silla de ruedas (wheelchair) Camello (camel) Pulpo (octopus) Seta (mushroom) Percha (hanger) La´piz (pencil) Embudo (funnel) Raqueta (racquet) Helico´ptero (helicopter) Bozal (muzzle) Ma´scara (mask) Acordeo´n (accordion) Espa´rrago (asparagus) Corona de flores (wreath) Volca´n (volcano) Bellota (acorn) Pira´mide (pyramid) Domino´ (dominoes) Pinzas (tongs) Compa´s (compass) Cactus (cactus) Armo´nica (harmonica) Rinoceronte (rhinoceros) Caballito de mar (seahorse) Magdalena (muffin) Arpa (harp) Globo terra´queo (globe) Trı´pode (tripod) Hamaca (hammock) Aldaba (knocker) Dardo (dart) Soga (noose) Pergamino (scroll) Paleta (palette) Canoa (canoe) Pelı´cano (pelican) Zancos (stilts) Yugo (yoke) Pestillo (latch) Iglu´ (igloo) Unicornio (unicorn) Esfinge (sphinx) Estetoscopio (stethoscope) ´ baco (abacus) A Castor (beaver) Transportador (protractor) Pe´rgola (trellis) Pretzel (pretzel)

A B C D D A B C C D A B B C D A A B C D D A B C C D A B B C D A A B C D D A B C C D A B B C D A A B C D D A B C C D A B

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Correct answer (%)

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Table 3. Shortened versions A, B, C, and D A

B

C

D

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15

Cama Escoba Banco Pulpo Seta Helico´ptero Corona de flores Pinzas Compa´s Magdalena Aldaba Canoa Pelı´cano Unicornio Transportador

´ rbol A Flor Silbato Escaleras meca´nicas Percha Bozal Volca´n Bellota Cactus Arpa Dardo Soga Zancos Esfinge Pe´rgola

Casa Cepillo de dientes Caracol Silla de ruedas La´piz Ma´scara Acordeo´n Pira´mide Harmo´nica Globo terra´queo Trı´pode Pergamino Yugo Estetoscopio ´ baco A

Tijeras Peine Sierra Camello Embudo Raqueta Espa´rrago Domino´ Rinoceronte Caballito de mar Hamaca Paleta Pestillo Iglu´ Castor

inconsequential, and the 95% CI test for statistical equivalence is satisfied (for an extensive description of the method, see Tryon, 2001). The present study predetermined a delta value of 3.2076 as a result of the following calculation: The lesser mean of the control sample minus the greater mean of the clinical sample of the shortened versions scores. We opted for this value because no agreed upon rationale for determining this value currently exists for the BNT shortened forms. To test equivalence using NHST the analysis of variance (ANOVA) and a post hoc analysis (Scheffe´), and Pearson’s correlation coefficients were conducted to examine differences and correlations in the four shortened versions scores. To analyze the adequacy of these shortened versions as an alternative to the 60-item BNT, Pearson’s correlation coefficients were calculated. All these analyses were carried out within the clinical sample. Considering that the ability to compare all co-normed test scores directly with each other facilitates clinical interpretation of neuropsychological test profiles, a uniform normative procedure was applied to all measures in the NEURONORMA project. Data management and characteristics of statistics analyses for the normative procedures of the entire project have been reported extensively in a previous paper (Pen˜a-Casanova, Blesa, et al., 2009). Briefly the procedure was the following: (a) the overlapping interval strategy (Pauker, 1988) was adopted to maximize the number of subjects contributing to the normative distribution at each midpoint age interval. Each midpoint age group provides norms for individuals of that age, plus or minus 1 year; (b) determination of age, sex, and education effects on raw subtest scores. Coefficients of correlation (r) and determination (R 2) of raw scores with age, years of education, and sex were determined for the BNT; (c) creation of age-adjusted normative tables. To ensure a normal distribution, the frequency distribution of the raw scores was converted into age-adjusted scaled scores, NSSA (NEURONORMA scaled score age-adjusted). For each age range, a cumulative frequency distribution of the raw scores was generated. Raw scores were assigned percentile ranks in function of their place within a distribution. Subsequently, percentile ranks were converted to scaled scores (from 2 to 18) based on percentile ranges. This transformation of raw scores to NSSA produced a distribution close to the normal distribution (mean ¼ 10; SD ¼ +3) on which linear regressions could be applied; (d) education adjustments. Years of education were modeled using the following equation: NSSA ¼ k + (b × Education). The regression coefficient (b) from this analysis was used as the basis for education adjustments. A linear regression was employed to derive age- and education-adjusted scaled scores. The following formula outlined by Mungas, Marshall, Weldon, Haan, and Reed (1996) was employed: NSSA&E = NSSA − b × [Education − 12]. The obtained value was truncated to the next lower integer. Results Table 1 summarizes the normative sample’s demographic characteristics. Age distribution of this control sample made it possible to calculate norms for the following 10 midpoint age groups: 50– 56, 57– 59, 60 – 62, 63– 65, 66– 68, 69– 71, 72– 74, 75– 77, 78– 80, .80. Sample sizes resulting from midpoint age intervals are presented in A, B, C, and D normative tables (Tables 9 – 12 and 14– 17). Means and standard deviations from the short-form versions of the normative and clinical sample are provided in Table 4. No significant statistical differences were found between all short-form versions when an ANOVA and a post hoc were

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Item

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Table 4. Mean comparisons of the four shortened versions A Normative sample (N ¼ 340) Mean (SD) 12.0424 (2.0858) Clinical sample (N ¼ 172) Mean (SD) 8.4410 (2.9492)

B

C

D

ANOVA

11.8970 (1.9086)

11.9515 (2.0296)

12.1000 (2.1591)

N.S.

8.3416 (2.9519)

8.6398 (2.7353)

8.6894 (2.6838)

N.S.

Table 5. Pearson’s correlation coefficient between the four shortened versions and the 60-item test within the clinical sample (N ¼ 172) A

B

C

D

1 .919a .933a .926a .928a

— 1 .804a .814a .779a

— — 1 .803a .846a

— — — 1 .822a

— — — — 1

a

p , .0001.

Table 6. Descriptive statistics for scores for A, B, C, and D shortened versions for the clinical sample Statistic

A

B

C

D

Mean SD N df (N 2 1) t (df) SE

8.4410 2.9492 161 160 1.9749 0.2324

8.3416 2.9519 161 160 1.9749 0.2326

8.6398 2.7353 161 160 1.9749 0.2156

8.6894 2.6838 161 160 1.9749 0.2115

Notes: t(df) ¼ t value associated to N –1 for an alfa of 0.05.

Table 7. 95% inferential confidence intervals and Rg values for scores for A, B, C, and D shortened versions B–A E tx A (95% CI) B (95% CI) C (95% CI) D (95% CI) Rg

0.7071 1.3965 Lower Upper Lower Upper Lower Upper Lower Upper

0.7076 1.3975 7.0445 9.8375 6.9451 9.7381

2.8923

B–C 0.7071 1.3965

6.9441 9.7391 7.2423 10.0373

3.0931

C–D 0.7076 1.3974

A –C 0.7079 1.3980 7.0435 9.8384

A–D

B–D

0.7079 1.3980 7.04300 9.8390 6.9435 9.7396

7.2433 10.0363 7.2929 10.0859 2.8426

7.2423 10.0372

2.9937

7.2914 10.0874 3.0444

7.2913 10.0874 3.1439

Notes: E and tx are necessary values to calculate the 95% inferential CI. For more details see Tryon, 2001; CI ¼ confidence interval; Rg ¼ the maximum probable difference associated with using different versions.

applied. The four short-form versions presented a satisfactory internal consistency when Cronbach’s alpha was calculated (A version: a . 0.75; B version: a . 0.76; C version: a . 0.74; D version: a . 0.78). Table 5 shows strong relationships among the four short-form versions as well as between each of them and the 60-item test based on Pearson’s correlation coefficient analysis tested within the clinical group. Table 6 shows the required statistics to carry out calculations to test equivalence. Based on these data, pairwise comparisons between the four shortened versions with the related inferential CIs and the resultant Rg are presented in Table 7. All the Rg values were less than 3.2076 for all combinations. Fig. 1 illustrates the inferential CIs plotted pairwise. We can appreciate that all the groups presented overlapping inferential CIs and an Rg less than the amount that substantively defines equivalence (Delta). Pearson’s correlations (r) and determination coefficient (R 2) of the four BNT short-form version scores with years of age, years of education, and sex are presented in Table 8. Age and education accounted significantly for the raw-score variance of all short-

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60-item test A B C D

60-item test

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Table 8. Correlations (r) and share variance (R2) of the four BNT shortened version scores with years of age, years of education, and sex Age (years)

A B C D

Education (years) 2

r

R

2.261 2.298 2.273 2.291

.068 .089 .075 .085

Sex 2

r

R

.435 .483 .588 .456

.189 .233 .346 .208

r

R2

2.096 2.085 2.085 2.093

.009 .007 .007 .009

form versions (R 2 . 0.05), indicative of a significant statistic effect of these variables on BNT total score. Sex differences were not observed in any of the four versions, indicating that no need to control this demographic variable. Age-adjusted NEURONORMA scaled scores (NSSA) for each BNT short-form version are provided in Tables 9 – 12 and include percentile ranks, ranges of ages contributing to each normative subsample, and the number of participants contributing to each test’s normative estimates. To use the table, select the appropriate column corresponding to the patient’s age, find the patient’s raw score, and subsequently refer to the corresponding NSSA and percentile rank (left part of the tables). As expected, the normative adjustments reduce shared variance of age to virtually ,1%. Education, however, continues to account significantly for age-adjusted test-score variance in all cases, up to 15% in all versions (Table 13). The transformation of raw scores to NSSA produced a distribution close to the normal distribution on which linear regressions could be applied. Regression coefficients from this analysis were used as the basis for education corrections. The resulting computational formulae were used to calculate NSSA&E (b ¼ 0.25243 for A version; b ¼ 0.26599 for B version; b ¼ 0.34083 for C version; b ¼ 0.24325 for D version). From these data, we have constructed adjustment tables for age and education for each version (Tables 14– 17). To use the tables, select the appropriate column corresponding to the patient’s years of education, find the patient’s NSSA, and subsequently refer to the corresponding NSSA&E.

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Fig. 1. Inferential CIs plotted pairwise.

68

M. Casals-Coll et al. / Archives of Clinical Neuropsychology 29 (2014) 60–74

Table 9. Age-adjusted NEURONORMA scores (NSSA) for the BNT A shortened version Scaled score

,1 1 2 3 –5 6 –10 11– 18 19– 28 29– 40 41– 59 60– 71 72– 81 82– 89 90– 94 95– 97 98 99 .99

Age range 50–56

57– 59

60– 62

63–65

66– 68

69– 71

72–74

75– 77

78– 80

81+

≤7

≤6 7

≤6 7

≤6

≤6

≤6

≤5

≤4 5

≤4 5

≤4

8 9 10

8

8

7– 8

7 –8

9 10 11 12 13

9 10 11 12 13

9 10 11 12 13

9 –10

7 8 9 10

6 7 8 9 10

11 12 13

11 12 13

11 12 13

11–12 13

5 6 7 8 –9 10 11 12 13

6 7 8– 9 10 11

6 7 8– 9 10 11

12

12 13

14 14

14

14

13 14

14

14 14

15 50–60 134

15 53– 63 132

15 56– 66 123

15 59–69 105

15 62– 72 118

14

15 65– 75 124

15 68–78 125

15 71– 81 100

14 15 74– 84 67

15 77–90 42

Table 10. Age-adjusted NEURONORMA scores (NSSA) for the BNT B shortened version Scaled score

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 Age range Sample size

Percentile range

,1 1 2 3 –5 6 –10 11– 18 19– 28 29– 40 41– 59 60– 71 72– 81 82– 89 90– 94 95– 97 98 99 .99

Age range 50–56

57– 59

60– 62

63–65

66– 68

69– 71

72–74

75– 77

78– 80

81+

≤7 8

≤7

≤7

≤6 7

≤6 7

≤6

≤5 6

≤5

≤5

≤5

9 10

8 9 10 11

12

12

12

8 9 10 11 12

7 8 9 10

10 11 12

6 7 8 9 10 11 12

6 7 8 9 10 11

6

8 9 10 11 12

7 8 9

11

8 9 10 11

13

13

13

13

13

12

12

13

13 13

13

14

14

14

14 14

15 50–60 134

15 53– 63 132

15 56– 66 123

11 12 13

7 8 9– 10 11

15 59–69 105

14 15 62– 72 118

14 15 65– 75 124

15 68–78 125

14 15 71– 81 100

14 14 15 74– 84 67

15 77–90 42

Discussion The main purpose of this report was to design four shortened versions as an alternative to the 60-item BNT in order to facilitate clinical assessment, to study the equivalence between the shortened versions in a clinical sample, and to provide normative data from a Spanish adult sample. Four shortened versions were proposed. Following an empirical procedure an item assignation to each version was carried out according to item difficulty analysis. This procedure is in line with other works (Saxton et al., 2000) and, even though a rigorous

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2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 Age range Sample size

Percentile range

M. Casals-Coll et al. / Archives of Clinical Neuropsychology 29 (2014) 60–74

69

Table 11. Age-adjusted NEURONORMA scores (NSSA) for the BNT C shortened version Scaled score

Age range

,1 1 2 3 –5 6 –10 11– 18 19– 28 29– 40 41– 59 60– 71 72– 81 82– 89 90– 94 95– 97 98 99 .99

50–56

57– 59

60–62

63–65

66– 68

69–71

72–74

75– 77

78–80

81+

≤9

≤6

≤6

≤6

≤5 6

≤6

≤5 6

≤5 6

≤5 6

≤5

7 8– 9

7 8 9 10 11 12

7 8 9 –10

7 8 9 10

7 8 –9 10

11 12

11 12

13 14

13 14

7 8 –9 10

10

11 12 13

11 12

14

10 11 12

10

13 14

6

11 12

13 14

7 8 9

13 13– 14

11 12 13 14

14

7

7

8– 9 10 11

8 9 –10 11

12 13

12 13

14 14 15 50–60 134

15 53– 63 132

15 56–66 123

15 59–69 105

15 62– 72 118

15 65–75 124

15 68–78 125

15 71– 81 100

15 74–84 67

15 77–90 42

Table 12. Age-adjusted NEURONORMA scores (NSSA) for the BNT D shortened version Scaled score

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 Age range Sample size

Percentile range

Age range

,1 1 2 3 –5 6 –10 11– 18 19– 28 29– 40 41– 59 60– 71 72– 81 82– 89 90– 94 95– 97 98 99 .99

50–56

57– 59

60–62

63–65

66– 68

69–71

72–74

75– 77

78–80

81+

≤7

≤6 7

≤7

≤6

≤6

≤5 6

≤5

≤4 5

≤4 5

≤4

7

7 7 8 9 10 11 12

6 –7 8 9

6 –7 8

10–11 12

13

13

8 9 10 11 12 13 14

8 9 10 11 12 13

8 9 10 11 12 13

8 9 10 11 12 13

8 9 10 11 12 13

14

14

14

14

5

9 10 11 12

15 53– 63 132

15 56–66 123

15 59–69 105

15 62– 72 118

10–11 12

13 14

15 50–60 134

6– 7 8 9

15 65–75 124

6 –7 8 9 10–11 12 13

13 14

14

15 68–78 125

15 71– 81 100

14 74–84 67

14 77–90 42

Table 13. Correlations (r) and share variance (R 2) of age-adjusted NEURONORMA scores (NSSA) with age and education Age (years)

A B C D

Education (years) 2

r

R

2.073 2.082 2.083 2.083

.005 .007 .007 .007

r

R2

.417 .459 .564 .389

.174 .211 .318 .151

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2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 Age range Sample size

Percentile range

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M. Casals-Coll et al. / Archives of Clinical Neuropsychology 29 (2014) 60–74

Table 14. Education adjustment for BNT A shortened version scale scores NSSA

0

1

2

3

4

5

6

7

8

9

10

11

12

13

14

15

16

17

18

19

20

5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

-1 0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15

Notes: Education adjustment by applying the following formula: NSSA&E ¼ NSSA – (b × [education – 12]), where b ¼ 0.25243.

Table 15. Education adjustment for BNT B shortened version scale scores NSSA

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

Education (years) 0

1

2

3

4

5

6

7

8

9

10

11

12

13

14

15

16

17

18

19

20

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

Notes: Education adjustment by applying the following formula: NSSA&E ¼ NSSA – (b × [education – 12]), where b ¼ 0.26599.

method to determine item difficulty for creation of these short forms was not used, the methodology utilized was superior to any arbitrary method. A satisfactory internal consistency was reported for each short-form version. It is interesting to note that high correlations were found among each short-form version and the original 60-item version when Pearson’s correlations were calculated with scores from the clinical sample. These results suggest that the four shortened versions would be a good alternative to the 60-item version. This study also examined equivalence of versions A, B, C, and D of the shortened BNT. Using traditional NHST, these versions were similar across scores. The results showed that there were no significant differences between the mean raw scores between the four short-form versions. Taking into account that NHST is an insufficient form of evidence to argue for form equivalence (Nickerson, 2000), we applied the Tryon’s method. Using the inferential CI method, the maximum probable difference between two means (Rg values) were calculated for each shortened version. This Rg was compared to the delta value that represents an amount considered inconsequential. In this study, it was specified a

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2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

Education (years)

M. Casals-Coll et al. / Archives of Clinical Neuropsychology 29 (2014) 60–74

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Table 16. Education adjustment for BNT C shortened version scale scores NSSA

0

1

2

3

4

5

6

7

8

9

10

11

12

13

14

15

16

17

18

19

20

6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21 22

5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21

5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21

5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

21 0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15

21 0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15

21 0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15

Notes: Education adjustment by applying the following formula: NSSA&E ¼ NSSA – (b × [education – 12]), where b ¼ 0.34083.

Table 17. Education adjustment for BNT D shortened version scale scores NSSA

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

Education (years) 0

1

2

3

4

5

6

7

8

9

10

11

12

13

14

15

16

17

18

19

20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

0 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16

Notes: Education adjustment by applying the following formula: NSSA&E ¼ NSSA – (b × [education – 12]), where b ¼ 0. 24325.

generic delta of 3.2076. We also opted for presenting the Rg values to allow comparisons criteria considering other uses of the shortened versions. All shortened versions showed Rg values below a delta of 3.2076; therefore, considering this value, the four versions would be equivalent. Consequently, these forms could be used interchangeably for most practical purposes in retest clinical assessment. These findings have important implications for neuropsychological assessment in a multidisciplinary clinical context in which effectiveness and efficiency are crucial. In order to obtain adjusted normative data from the four short-form versions, sociodemographic factors were analyzed. The results showed that raw scores of all versions were influenced by education and age. This finding is in agreement with previous studies that observed significant effects of age on shortened BNT version scores (Fastenau et al., 1998). We found a weak correlation between age and the scores obtained in the four short-form versions of the BNT. This correlation was weak probably because

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2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18

Education (years)

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Funding This study was mainly supported by a grant from the Pfizer Foundation and by the Medical Department of Pfizer, SA, Spain. It was also supported by the Neurofunctionality of Brain and Language group of the Program of Neurosciences of the Institut Hospital del Mar d’Investigacions Me`diques, Barcelona, Spain. JP-C has received an intensification research grant from the CIBERNED (Centro de Investigacio´n Biome´dica en Red sobre Enfermedades Neurodegenerativas), Instituto Carlos III (Ministry of Health & Consumer Affairs of Spain). Conflict of Interest None declared.

Appendix: Members of the NEURONORMAES Study Team Steering Committee: JP-C, Hospital del Mar, Barcelona, Spain; RB, Hospital de la Santa Creu i Sant Pau, Barcelona, Spain; MA, Hospital Mu´tua de Terrassa, Terrassa, Spain. Principal Investigators: JP-C, Hospital del Mar, Barcelona, Spain; RB, Hospital de la Santa Creu i Sant Pau, Barcelona, Spain; MA, Hospital Mu´tua de Terrassa, Terrassa, Spain; JLM, Hospital Clı´nic, Barcelona, Spain; AR, Hospital Clı´nico Universitario, Santiago de Compostela, Spain; MSB (deceased), Hospital Clı´nico San Carlos, Madrid, Spain; CA, Hospital Virgen Arrixaca, Murcia, Spain; CM-P, Hospital Virgen Macarena, Sevilla, Spain; AF-G, Hospital Universitario La Paz, Madrid, Spain; MF, Hospital de Cruces, Bilbao, Spain. Genetics substudy: RO, Service of Genetics, Hospital Clı´nic, Barcelona, Spain. Neuroimaging substudy: BG-A, Radiology Department and IDIBAPS, Hospital Clı´nic, Barcelona, Spain. Research Fellows: Gemma Monte, Elena Alayrach, Aitor Sainz, and Claudia Caprile, Fundacio´ Clı´nic, Hospital Clı´nic, Barcelona, Spain; Gonzalo Sa´nchez, Behavioral Neurology Group, Institut Municipal d’Investigacio´ Me`dica. Barcelona, Spain. Clinicians, Psychologists, and Neuropsychologists: Nina Gramunt (coordinator), Peter Bo¨hm, Sonia Gonza´lez, Yolanda Buriel, Marı´a Quintana, Sonia Quin˜ones, Gonzalo Sa´nchez, Rosa M. Manero, Gracia Cucurella, Institut Municipal d’Investigacio´ Me`dica, Barcelona, Spain; Eva Ruiz, Mo´nica Serradell, Laura Torner, Hospital Clı´nic, Barcelona, Spain;

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of the range of age observed. We could hypothesize that more differences had been found in a sample with a wider range of age. When normative adjustments were applied, the variance produced by age was minimized. Similarly, education had a significant impact on raw scores. These results are consistent with other reports which found years of education to have a considerable influence on BNT scores (Jefferson et al., 2007; Lansing et al., 1999; Ponto´n et al., 1996; Saxton et al., 2000; Tombaugh & Hubley, 1997). It is important to clarify that we included a group of participants with 0 – 5 years of education. This group of low educated subjects, even if commonly seen for the post-war generations in Spain, could have probably driven the results. In a similar manner to previous reports (Calero et al., 2002), sex did not affect the raw scores of any of the shortened versions tested in this study. The combination of these findings supports the use of these shortened versions for clinical assessment and research. Even so, this study presents limitations. The most important one lies in the fact that these data stemmed from the 60-item version administration. However, in reviewing the literature (Lansing et al., 1999; Mack et al., 1992; Saxton et al., 2000), it could be hypothesized that our results would have been similar if data had been originated from separate administrations. This procedure facilitates control of some confounding variables, such as test retest variability. Additionally, as the BNT normative study of the NEURONORMA project justified (Pen˜a-Casanova, Quin˜ones-Ubeda, et al., 2009), this study utilized the word “magdalena” as an alternative to “pretzel” because of its extremely low frequency of correct responses presented in a Spanish control sample. As a result, the four short-form versions maintained the original items but changed “pretzel” for “magadalena.” This condition confers some difficulties when comparing the results of this study to previous Spanish studies data. Finally, as in all normative studies, the validity of these norms is clearly dependent upon the similarity between the characteristics of the studied subjects and the demographic features of the normative sample. Despite the fact that some American countries share the same language with Spain, cultural and linguistic differences do exist. Therefore, it would be advisable to apply these norms with caution to these other Spanish speaking populations. For future research, and in order to establish the adaptation of these BNT norms, it would be interesting to study the test performance in these populations. In summary, this paper presents normative data for 15-item specially designed shortened versions of the BNT. Our data show good equivalence among the shortened versions of the BNT. In addition, the four short-forms are presented as a good alternative to the original BNT. As a result, the four 15-item versions can be used instead of the original BNT for screening purposes.

M. Casals-Coll et al. / Archives of Clinical Neuropsychology 29 (2014) 60–74

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Dolors Badenes, Laura Casas, Noemı´ Cerulla, Silvia Ramos, Loli Cabello, Hospital Mu´tua de Terrassa, Terrassa, Spain; Dolores Rodrı´guez, Clinical Psychology and Psychobiology Department, University of Santiago de Compostela, Spain; Marı´a Payno, Clara Villanueva, Hospital Clı´nico San Carlos, Madrid, Spain; Rafael Carles, Judit Jime´nez, Martirio Antequera, Hospital Virgen Arixaca, Murcia, Spain; Jose Manuel Gata, Pablo Duque, Laura Jime´nez, Hospital Virgen Macarena, Sevilla, Spain; Azucena Sanz, Marı´a Dolores Aguilar, Hospital Universitario La Paz, Madrid, Spain; Ana Molano, Maitena Lasa, Hospital de Cruces, Bilbao, Spain. Administrative Management: Carme Pla (deceased), Romina Ribas, Department of Psychiatry and Forensic Medicine, Universitat Auto`noma de Barcelona, and Behavioral Neurology Group, Institut Municipal d’Investigacio´ Me`dica, Barcelona, Spain. References Downloaded from http://acn.oxfordjournals.org/ at The University of British Colombia Library on June 18, 2015

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Spanish multicenter normative studies (NEURONORMA project): normative data and equivalence of four BNT short-form versions.

The application of the Boston Naming Test (BNT) is time-consuming and shortened versions need to be developed for screening purposes. The aims of this...
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