British Journal of Social Psychology ( IF 3.2 ) Pub Date : 2021-06-17 , DOI: 10.1111/bjso.12461
Correction in the paper by Kotzur et al. (2020), ‘Society thinks they are cold and/or incompetent, but I do not’, stereotype content ratings depend on instructions and the social group's location in the stereotype content space.
While doing reanalysis, the authors noticed two errors in the preliminary analyses. The authors mistakenly freed one equality constraint too many during the partial measurement testing in study 2, group Turks (Table 5), and study 3, group Bulgarians (Table 8). The error did not substantially influence the subsequent mean value comparisons (Tables 6 and 9). The main message of the studies also remained the same. That is, the direction and significance of the affected coefficients remained the same, only the size changed a little. The corrected tables (Tables 5, 6, 8, and 9) are as below, with changed parameters highlighted in bold:
n | df | p | /df | RMSEA | CFI | SRMR | Δ | Δdf | p | ||
---|---|---|---|---|---|---|---|---|---|---|---|
Elderly | |||||||||||
Configural | 126 | 53.66 | 42 | .107 | 1.28 | .05 | .96 | .07 | |||
Metric | 126 | 54.34 | 46 | .187 | 1.18 | .04 | .97 | .08 | 1.47 | 4 | .832 |
Scalar | 126 | 57.32 | 50 | .222 | 1.15 | .03 | .97 | .08 | 3.11 | 4 | .539 |
Jobless | |||||||||||
Configural | 126 | 84.20 | 64 | .046 | 1.32 | .05 | .96 | .08 | |||
Metric | 126 | 98.02 | 69 | .012 | 1.42 | .06 | .94 | .09 | 13.26 | 5 | .021 |
Partial metric | 126 | 84.80 | 68 | .082 | 1.25 | .04 | .97 | .08 | 0.94 | 4 | .919 |
Scalar | 126 | 91.64 | 71 | .050 | 1.29 | .05 | .96 | .08 | 7.26 | 3 | .064 |
Physicians | |||||||||||
Configural | 126 | 145.79 | 90 | .000 | 1.62 | .07 | .91 | .08 | |||
Rich | |||||||||||
Configural | 126 | 54.81 | 42 | .089 | 1.30 | .05 | .97 | .06 | |||
Metric | 126 | 59.08 | 46 | .093 | 1.64 | .05 | .97 | .06 | 4.40 | 4 | .355 |
Scalar | 126 | 66.51 | 50 | .059 | 1.33 | .05 | .96 | .06 | 7.64 | 4 | .106 |
Turks | |||||||||||
Configurala
a
Includes Haywood case. We refrained from testing for metric and scalar invariance for physicians, since the previous model did not reach configural invariance. Δ, Δdf, and p refer to chi-square difference test results with the Satorra–Bentler scaling correction (more freely estimated model vs. more constrained model). |
126 | 48.22 | 42 | .236 | 1.15 | .03 | .98 | .06 | |||
Metrica
a
Includes Haywood case. We refrained from testing for metric and scalar invariance for physicians, since the previous model did not reach configural invariance. Δ, Δdf, and p refer to chi-square difference test results with the Satorra–Bentler scaling correction (more freely estimated model vs. more constrained model). |
126 | 60.56 | 46 | .074 | 1.32 | .05 | .96 | .09 | 12.68 | 4 | .013 |
Partial metrica
a
Includes Haywood case. We refrained from testing for metric and scalar invariance for physicians, since the previous model did not reach configural invariance. Δ, Δdf, and p refer to chi-square difference test results with the Satorra–Bentler scaling correction (more freely estimated model vs. more constrained model). |
126 | 53.14 | 45 | .189 | 1.18 | .04 | .98 | .07 | 4.95 | 3 | .176 |
Scalara
a
Includes Haywood case. We refrained from testing for metric and scalar invariance for physicians, since the previous model did not reach configural invariance. Δ, Δdf, and p refer to chi-square difference test results with the Satorra–Bentler scaling correction (more freely estimated model vs. more constrained model). |
126 | 60.13 | 49 | .132 | 1.23 | .04 | .97 | .09 | 7.04 | 4 | .134 |
Note
- For elderly, rich, and Turks, we considered a model in which the items warm, confident, competitive, and tolerant were excluded (see Table 4). For jobless, we considered a model in which the items warm, confident, and competitive were excluded (see Table S5). For physicians, we considered a model in which the items warm and confident were excluded (see Table S3).
- a Includes Haywood case. We refrained from testing for metric and scalar invariance for physicians, since the previous model did not reach configural invariance. Δ, Δdf, and p refer to chi-square difference test results with the Satorra–Bentler scaling correction (more freely estimated model vs. more constrained model).
Warmth | Competence | |||||
---|---|---|---|---|---|---|
Estimate | SE | p | Estimate | SE | p | |
Elderly | −0.02 | 0.06 | .770 | 0.14 | 0.07 | .043 |
Jobless | 0.57 | 0.18 | .002 | 0.80 | 0.15 | <.001 |
Rich | 0.30 | 0.08 | .000 | −0.10 | 0.07 | .134 |
Turks | 0.42 | 0.06 | <.001 | 0.36 | 0.06 | <.001 |
Note
- Society’s perspective condition served as a reference group (latent mean = 0).
N | df | p | /df | RMSEA | CFI | SRMR | Δ | Δdf | p | ||
---|---|---|---|---|---|---|---|---|---|---|---|
Albanian | |||||||||||
Configural | 131 | 4.66 | 16 | .997 | 0.29 | .00 | 1.00 | .02 | |||
Metric | 131 | 11.51 | 20 | .932 | 0.58 | .00 | 1.00 | .08 | 9.41 | 4 | .052 |
Scalar | 131 | 14.19 | 24 | .942 | 0.59 | .00 | 1.00 | .07 | 2.82 | 4 | .589 |
Bulgarian | |||||||||||
Configural | 119 | 28.44 | 26 | .337 | 1.09 | .04 | .99 | .04 | |||
Metric | 119 | 40.52 | 31 | .118 | 1.31 | .07 | .97 | .11 | 13.56 | 5 | .019 |
Partial metric | 119 | 34.67 | 30 | .255 | 1.16 | .05 | .99 | .08 | 6.91 | 4 | .141 |
Scalar | 119 | 41.85 | 35 | .198 | 1.20 | .06 | .98 | .10 | 7.33 | 5 | .197 |
German | |||||||||||
Configural | 117 | 32.07 | 26 | .191 | 1.23 | .06 | .97 | .05 | |||
Metric | 117 | 45.99 | 31 | .041 | 1.48 | .09 | .92 | .14 | 12.37 | 5 | .030 |
Partial metric | 117 | 40.48 | 30 | .096 | 1.35 | .08 | .94 | .12 | 7.74 | 4 | .101 |
Italian | |||||||||||
Configural | 108 | 18.88 | 16 | .275 | 1.18 | .06 | .99 | .05 | |||
Metric | 108 | 24.36 | 20 | .227 | 1.22 | .06 | .98 | .10 | 5.49 | 4 | .241 |
Scalar | 108 | 27.37 | 24 | .288 | 1.14 | .05 | .99 | .11 | 2.78 | 4 | .595 |
Moroccan | |||||||||||
Configural | 94 | 23.90 | 26 | .582 | 0.92 | .00 | 1.00 | .02 | |||
Metric | 94 | 26.23 | 31 | .710 | 0.85 | .00 | 1.00 | .04 | 2.19 | 5 | .823 |
Scalar | 94 | 33.57 | 36 | .585 | 0.93 | .00 | 1.00 | .05 | 7.66 | 5 | .176 |
Pakistani | |||||||||||
Configural | 120 | 35.71 | 26 | .097 | 1.37 | .08 | .98 | .03 | |||
Metric | 120 | 41.08 | 31 | .106 | 1.33 | .07 | .98 | .06 | 5.18 | 5 | .823 |
Scalar | 120 | 50.07 | 36 | .060 | 1.39 | .08 | .97 | .07 | 9.58 | 5 | .088 |
Polish | |||||||||||
Configural | 112 | 14.38 | 16 | .571 | 0.90 | .00 | 1.00 | .03 | |||
Metric | 112 | 18.81 | 20 | .534 | 0.94 | .00 | 1.00 | .07 | 4.83 | 4 | .305 |
Scalar | 112 | 23.82 | 24 | .472 | 0.99 | .00 | 1.00 | .09 | 5.09 | 4 | .278 |
Turkish | |||||||||||
Configural | 123 | 17.17 | 16 | .375 | 1.07 | .03 | 1.00 | .03 | |||
Metric | 123 | 21.86 | 20 | .348 | 1.09 | .04 | 1.00 | .06 | 4.68 | 4 | .321 |
Scalar | 123 | 22.27 | 24 | .563 | 0.93 | .00 | 1.00 | .07 | 0.55 | 4 | .968 |
Note
- For Germans and Bulgarian, Moroccan, and Pakistani migrants, we considered a model in which the item cold–warm was excluded (see Table S7). For Albanian, Italian, Polish, and Turkish migrants, we considered a model in which the items cold–warm and uneducated–highly educated were excluded (see Table 7). We refrained from testing for scalar invariance for Germans, since the partial metric model did not meet model fit requirements. We refrained from submitting Italian migrants to further analyses, since the model fit of the scalar model was below cut-off criteria. Δ, Δdf, and p refer to chi-square difference test results with the Satorra–Bentler scaling correction (more freely estimated model vs. more constrained model).
Warmth | Competence | |||||||
---|---|---|---|---|---|---|---|---|
Estimate | SE | p | Power | Estimate | SE | p | Power | |
Albanian | 0.55 | 0.24 | .020 | .96 | 0.52 | 0.18 | .004 | .99 |
Bulgarian | 0.67 | 0.27 | .015 | .94 | 0.42 | 0.18 | .018 | .97 |
Moroccan | 0.42 | 0.26 | .112 | .73 | 0.32 | 0.26 | .223 | .40 |
Pakistani | 0.49 | 0.25 | .004 | .90 | 0.36 | 0.23 | .118 | .69 |
Polish | 0.37 | 0.25 | .145 | .55 | 0.15 | 0.24 | .526 | .14 |
Turkish | 0.58 | 0.25 | .020 | .97 | 0.45 | 0.21 | .036 | .94 |
Note
- Society’s perspective condition served as a reference group (latent mean = 0). Power refers to the post-hoc power estimates obtained using the Monte Carlo simulations with 10,000 replications and MLR estimator, assuming normally distributed and complete data (Muthén & Muthén, 2002).
The same two errors required adjustments to the sentences in which the authors referred to the coefficients on pages 1027 and 1033.
On page 1027 (last paragraph), the value for Kappa (K) changes from ‘0.44’ to ‘0.42’, so the text reads as ‘as well as Turks, K = 0.42, p < .001, and K = 0.36, p < .001, respectively’.
On page 1033 (last paragraph), the value for Kappa (K) changes from ‘0.75’ to ‘0.67’ and from ‘0.59’ to ‘0.42’; the p-value changed from ‘.004’ to ‘.015’ and from ‘.001’ to ‘.018’, so the text reads as ‘Bulgarian migrants, K = 0.67, p = .015, and K = 0.42, p = .018’.
We sincerely apologize for any inconvenience this may have caused.
中文翻译:
更正
Kotzur 等人在论文中的更正。(2020 年),“社会认为他们冷漠和/或无能,但我不认为”,刻板印象内容评级取决于指令和社会群体在刻板印象内容空间中的位置。
在进行再分析时,作者注意到初步分析中有两个错误。在研究 2 土耳其人组(表 5)和研究 3 保加利亚人组(表 8)的部分测量测试中,作者错误地释放了一个等式约束太多。该误差对随后的平均值比较没有实质性影响(表 6 和 9)。研究的主要信息也保持不变。即受影响系数的方向和显着性保持不变,只是大小略有变化。更正后的表(表 5、6、8 和 9)如下,更改的参数以粗体突出显示:
n | df | 磷 | /df | RMSEA | CFI | SRMR | Δ | Δ DF | 磷 | ||
---|---|---|---|---|---|---|---|---|---|---|---|
老年 | |||||||||||
配置的 | 126 | 53.66 | 42 | .107 | 1.28 | .05 | .96 | .07 | |||
公制 | 126 | 54.34 | 46 | .187 | 1.18 | .04 | .97 | .08 | 1.47 | 4 | .832 |
标量 | 126 | 57.32 | 50 | .222 | 1.15 | .03 | .97 | .08 | 3.11 | 4 | .539 |
失业 | |||||||||||
配置的 | 126 | 84.20 | 64 | .046 | 1.32 | .05 | .96 | .08 | |||
公制 | 126 | 98.02 | 69 | .012 | 1.42 | .06 | .94 | .09 | 13.26 | 5 | .021 |
部分指标 | 126 | 84.80 | 68 | .082 | 1.25 | .04 | .97 | .08 | 0.94 | 4 | .919 |
标量 | 126 | 91.64 | 71 | .050 | 1.29 | .05 | .96 | .08 | 7.26 | 3 | .064 |
医师 | |||||||||||
配置的 | 126 | 145.79 | 90 | .000 | 1.62 | .07 | .91 | .08 | |||
富有的 | |||||||||||
配置的 | 126 | 54.81 | 42 | .089 | 1.30 | .05 | .97 | .06 | |||
公制 | 126 | 59.08 | 46 | .093 | 1.64 | .05 | .97 | .06 | 4.40 | 4 | .355 |
标量 | 126 | 66.51 | 50 | .059 | 1.33 | .05 | .96 | .06 | 7.64 | 4 | .106 |
土耳其人 | |||||||||||
配置一个
a
包括海伍德案。我们避免测试医生的度量和标量不变性,因为之前的模型没有达到配置不变性。Δ、Δ df和p是指使用 Satorra-Bentler 标度校正(更自由估计的模型与更受约束的模型)的卡方差异检验结果。 |
126 | 48.22 | 42 | .236 | 1.15 | .03 | .98 | .06 | |||
公制a
a
包括海伍德案。我们避免测试医生的度量和标量不变性,因为之前的模型没有达到配置不变性。Δ、Δ df和p是指使用 Satorra-Bentler 标度校正(更自由估计的模型与更受约束的模型)的卡方差异检验结果。 |
126 | 60.56 | 46 | .074 | 1.32 | .05 | .96 | .09 | 12.68 | 4 | .013 |
部分度量a
a
包括海伍德案。我们避免测试医生的度量和标量不变性,因为之前的模型没有达到配置不变性。Δ、Δ df和p是指使用 Satorra-Bentler 标度校正(更自由估计的模型与更受约束的模型)的卡方差异检验结果。 |
126 | 53.14 | 45 | .189 | 1.18 | .04 | .98 | .07 | 4.95 | 3 | .176 |
标量a
a
包括海伍德案。我们避免测试医生的度量和标量不变性,因为之前的模型没有达到配置不变性。Δ、Δ df和p是指使用 Satorra-Bentler 标度校正(更自由估计的模型与更受约束的模型)的卡方差异检验结果。 |
126 | 60.13 | 49 | .132 | 1.23 | .04 | .97 | .09 | 7.04 | 4 | .134 |
笔记
- 对于老年人、富人和土耳其人,我们考虑了一个模型,其中排除了热情、自信、有竞争力和宽容的项目(见表 4)。对于失业者,我们考虑了一个模型,其中排除了热情、自信和有竞争力的项目(见表 S5)。对于医生,我们考虑了一个模型,其中排除了热情和自信的项目(见表 S3)。
- a 包括海伍德案。我们避免测试医生的度量和标量不变性,因为之前的模型没有达到配置不变性。Δ、Δ df和p是指使用 Satorra-Bentler 标度校正(更自由估计的模型与更受约束的模型)的卡方差异检验结果。
温暖 | 权限 | |||||
---|---|---|---|---|---|---|
估计 | 东南 | 磷 | 估计 | 东南 | 磷 | |
老年 | −0.02 | 0.06 | .770 | 0.14 | 0.07 | .043 |
失业 | 0.57 | 0.18 | .002 | 0.80 | 0.15 | <.001 |
富有的 | 0.30 | 0.08 | .000 | −0.10 | 0.07 | .134 |
土耳其人 | 0.42 | 0.06 | <.001 | 0.36 | 0.06 | <.001 |
笔记
- 社会的视角条件作为参考组(潜在均值 = 0)。
N | df | 磷 | /df | RMSEA | CFI | SRMR | Δ | Δ DF | 磷 | ||
---|---|---|---|---|---|---|---|---|---|---|---|
阿尔巴尼亚语 | |||||||||||
配置的 | 131 | 4.66 | 16 | .997 | 0.29 | .00 | 1.00 | .02 | |||
公制 | 131 | 11.51 | 20 | .932 | 0.58 | .00 | 1.00 | .08 | 9.41 | 4 | .052 |
标量 | 131 | 14.19 | 24 | .942 | 0.59 | .00 | 1.00 | .07 | 2.82 | 4 | .589 |
保加利亚语 | |||||||||||
配置的 | 119 | 28.44 | 26 | .337 | 1.09 | .04 | .99 | .04 | |||
公制 | 119 | 40.52 | 31 | .118 | 1.31 | .07 | .97 | .11 | 13.56 | 5 | .019 |
部分指标 | 119 | 34.67 | 30 | .255 | 1.16 | .05 | .99 | .08 | 6.91 | 4 | .141 |
标量 | 119 | 41.85 | 35 | .198 | 1.20 | .06 | .98 | .10 | 7.33 | 5 | .197 |
德语 | |||||||||||
配置的 | 117 | 32.07 | 26 | .191 | 1.23 | .06 | .97 | .05 | |||
公制 | 117 | 45.99 | 31 | .041 | 1.48 | .09 | .92 | .14 | 12.37 | 5 | .030 |
部分指标 | 117 | 40.48 | 30 | .096 | 1.35 | .08 | .94 | .12 | 7.74 | 4 | .101 |
意大利语 | |||||||||||
配置的 | 108 | 18.88 | 16 | .275 | 1.18 | .06 | .99 | .05 | |||
公制 | 108 | 24.36 | 20 | .227 | 1.22 | .06 | .98 | .10 | 5.49 | 4 | .241 |
标量 | 108 | 27.37 | 24 | .288 | 1.14 | .05 | .99 | .11 | 2.78 | 4 | .595 |
摩洛哥 | |||||||||||
配置的 | 94 | 23.90 | 26 | .582 | 0.92 | .00 | 1.00 | .02 | |||
公制 | 94 | 26.23 | 31 | .710 | 0.85 | .00 | 1.00 | .04 | 2.19 | 5 | .823 |
标量 | 94 | 33.57 | 36 | .585 | 0.93 | .00 | 1.00 | .05 | 7.66 | 5 | .176 |
巴基斯坦 | |||||||||||
配置的 | 120 | 35.71 | 26 | .097 | 1.37 | .08 | .98 | .03 | |||
公制 | 120 | 41.08 | 31 | .106 | 1.33 | .07 | .98 | .06 | 5.18 | 5 | .823 |
标量 | 120 | 50.07 | 36 | .060 | 1.39 | .08 | .97 | .07 | 9.58 | 5 | .088 |
抛光 | |||||||||||
配置的 | 112 | 14.38 | 16 | .571 | 0.90 | .00 | 1.00 | .03 | |||
公制 | 112 | 18.81 | 20 | .534 | 0.94 | .00 | 1.00 | .07 | 4.83 | 4 | .305 |
标量 | 112 | 23.82 | 24 | .472 | 0.99 | .00 | 1.00 | .09 | 5.09 | 4 | .278 |
土耳其 | |||||||||||
配置的 | 123 | 17.17 | 16 | .375 | 1.07 | .03 | 1.00 | .03 | |||
公制 | 123 | 21.86 | 20 | .348 | 1.09 | .04 | 1.00 | .06 | 4.68 | 4 | .321 |
标量 | 123 | 22.27 | 24 | .563 | 0.93 | .00 | 1.00 | .07 | 0.55 | 4 | .968 |
笔记
- 对于德国人和保加利亚人、摩洛哥人和巴基斯坦人的移民,我们考虑了一个模型,其中排除了冷-暖项目(见表 S7)。对于阿尔巴尼亚、意大利、波兰和土耳其移民,我们考虑了一个模型,其中排除了冷 - 温暖和未受过教育 - 受过高等教育的项目(见表 7)。我们避免测试德国人的标量不变性,因为部分度量模型不符合模型拟合要求。我们避免将意大利移民提交进一步分析,因为标量模型的模型拟合低于截止标准。Δ 、Δ df和p是指使用 Satorra-Bentler 标度校正(更自由估计的模型与更受约束的模型)的卡方差异检验结果。
温暖 | 权限 | |||||||
---|---|---|---|---|---|---|---|---|
估计 | 东南 | 磷 | 力量 | 估计 | 东南 | 磷 | 力量 | |
阿尔巴尼亚语 | 0.55 | 0.24 | .020 | .96 | 0.52 | 0.18 | .004 | .99 |
保加利亚语 | 0.67 | 0.27 | .015 | .94 | 0.42 | 0.18 | .018 | .97 |
摩洛哥 | 0.42 | 0.26 | .112 | .73 | 0.32 | 0.26 | .223 | .40 |
巴基斯坦 | 0.49 | 0.25 | .004 | .90 | 0.36 | 0.23 | .118 | .69 |
抛光 | 0.37 | 0.25 | .145 | .55 | 0.15 | 0.24 | .526 | .14 |
土耳其 | 0.58 | 0.25 | .020 | .97 | 0.45 | 0.21 | .036 | .94 |
笔记
- 社会的视角条件作为参考组(潜在均值 = 0)。功效是指使用具有 10,000 次重复的蒙特卡罗模拟和 MLR 估计器获得的事后功效估计,假设数据为正态分布和完整数据 (Muthén & Muthén, 2002)。
同样的两个错误需要对作者提到第 1027 页和第 1033 页上的系数的句子进行调整。
在第 1027 页(最后一段)上,Kappa (K) 的值从“0.44”变为“0.42”,因此文本读作“以及土耳其人,K = 0.42,p < .001,并且 K = 0.36,p < .001,分别'。
在第 1033 页(最后一段)上,Kappa (K) 的值从“0.75”更改为“0.67”,从“0.59”更改为“0.42”;的p -值从变化“0.004'向” 0.015' ,并从“0.001'向” 0.018' ,因此文本读为保加利亚移民,K = 0.67 ,P = 0.015和K = 0.42,p = .018'。
对于由此可能造成的任何不便,我们深表歉意。