The traditional understanding of data from Likert scales is that the quantifications involved result from measures of attitude strength. Applying a recently proposed semantic theory of survey response, we claim that survey responses tap two different sources: a mixture of attitudes plus the semantic structure of the survey. Exploring the degree to which individual responses are influenced by semantics, we hypothesized that in many cases, information about attitude strength is actually filtered out as noise in the commonly used correlation matrix. We developed a procedure to separate the semantic influence from attitude strength in individual response patterns, and compared these results to, respectively, the observed sample correlation matrices and the semantic similarity structures arising from text analysis algorithms. This was done with four datasets, comprising a total of 7,787 subjects and 27,461,502 observed item pair responses. As we argued, attitude strength seemed to account for much information about the individual respondents. However, this information did not seem to carry over into the observed sample correlation matrices, which instead converged around the semantic structures offered by the survey items. This is potentially disturbing for the traditional understanding of what survey data represent. We argue that this approach contributes to a better understanding of the cognitive processes involved in survey responses. In turn, this could help us make better use of the data that such methods provide.
What do the numbers in survey statistics measure—what do they represent? A growing series of studies have shown that the statistical properties of survey research are partly or even largely predictable a priori because of their semantic structures (Arnulf & Larsen, 2015; Arnulf, Larsen, Martinsen, & Bong, 2014; Gefen & Larsen, 2017; Larsen & Bong, 2013; Nimon, Shuck, & Zigarmi, 2015). Statistical patterns in responses may therefore express more of the respondents’ cognitive operations than of their attitudes, as is explained in the recently proposed semantic theory of survey response (STSR; Arnulf et al., 2014; Arnulf, Larsen, Martinsen, & Bong, 2015).
In his original work on response scales, Likert (1932) was insistent that the object of measurement should be attitude strength. If the emerging statistics are caused by other psychological operations, such as the cognitive processing of items, it would cast doubt about their nature as measurements and pose a problem for interpretation (Lamiell, 2013; Slaney & Racine, 2013). On the other hand, the possibility to explore and measure these cognitive operations might open new applications in survey research, possibly improving the predictive validity of such measurements and expanding the use of such instruments.
The purpose of this study is to show how commonly applied statistical techniques actually may frequently filter out its purported subject matter—that is, attitude strength—leaving only traces of cognitive language parsing operations, contrary to central assumptions in construct validation (American Educational Research Association, American Psychological Association, and National Council on Measurement in Education, 2014; Cronbach & Meehl, 1955; MacKenzie, Podsakoff, & Podsakoff, 2011). This is important for at least two reasons: Primarily, establishing a model of the cognitive framework activated in survey responses can give us more knowledge about how attitudes and mental models are connected. Secondarily, it is principally a serious concern for the interpretation of psychometric models if the numbers are representing a different phenomenon than commonly purported.
Since Likert published his scales for assessing attitudes 80 years ago (Likert, 1932), they have turned into one of the most prevalent methods of social science in general, and of organizational behavior (OB) in particular (Cascio, 2012). Respondents assign numbers (or answer in categories later translated to numbers), and the numbers should reflect the degrees to which they endorse the survey items (MacKenzie et al., 2011; Michell, 2013; Nunnally & Bernstein, 2010). Increasingly sophisticated statistical procedures are applied to analyze patterns in the ensuing statistics, and common to many of these is that they take the covariance or correlation matrix as their point of departure (Borsboom, 2008; Jöreskog, 1993). Yet, researchers have intermittently published suspicions concerning the role of cognitive processes involved in reading and processing the items. These may influence the observed statistics, distort measures, or even create artificial numbers in cases in which respondents do not really hold any attitudes (Borsboom, 2009; Feldman & Lynch, 1988; Maul, 2017; Schwarz, 1999).
With the development of digital text analysis in recent years, the cognitive properties of survey items are now open to direct assessment. Recent studies have applied various semantic algorithms to compute overlap in meaning among frequently used Likert scales across fields such as OB and information science (IS). Text algorithms alone were able to explain between 54 and 86% of the variation in correlation matrices from leadership research (Arnulf et al., 2014), displayed comparable factor structures in surveys on IS (Gefen & Larsen, 2017), and demonstrated wide semantic overlap between employee engagement and job satisfaction (Nimon et al., 2015). Semantic properties do not always seem to play an important role, as in the personality test NEO-FFI in which semantics had negligible predictive value (Arnulf et al., 2014). As yet there is no theoretical or empirical framework to explain the reason why stable personality traits such as the Big Five may not be as semantically predictable as the responses to surveys on perceptions in organizations.
This study aims to explore and explain why semantics may influence survey statistics by developing a way to track the influence of semantic operations in individual response patterns. By using an individual level analysis, we can track the sources of influence on individual response patterns and determine which aspects of individual respondents that are most likely to accumulate and determine the ensuing sample statistics. The data materials in this study will be the same four datasets as used in Arnulf et al.’s (2014) study, but this time broken down to the level of individual responses. This kind of reanalysis is important because the previous study merely documented the influence of semantics on the sample statistics. To explain why semantics may explain between the negligible and 86% of observed variation in samples, the separate sources of variation in individual responses need to be assessed. For example, if responses measuring stable personality traits are indeed different from responses to shifting perceptions, we need more incisive methods to explore and explain this. The present study is also a methodological innovation, since there is no previously established way to disentangle semantics from attitude strength in survey data. For this reason, we also refrain from stating hypotheses, but stick to outlining the methodological steps and report the ensuing findings.
Attitude strength and semantic relationships
The relationship between semantics and attitude strength is well illustrated by Bertrand Russell’s introduction to Wittgenstein’s Tractatus Logico-Philosophicus (1922). Here, the two philosophers make a distinction between three types of scientific facts: empirical, psychological, and logical facts.
Take as an example the sentence “It is raining.” The “empirical” fact would be a demonstration of whether or not it is raining. A “psychological” fact would be whether someone believes it to be raining. The “logical” fact, however, is likely to be taken for granted by many people, but still reflects a cognitive process in the brain: The expression “It is raining” needs to be logically comprehensible and recognizably different from other statements. This condition is, de facto, a prerequisite for the other two: believing in rain and possibly falsifying its empirical justification.
Generally, the object of empirical science is to establish empirical facts, such that people with different opinions (in the state of harboring different psychological facts) can subsequently agree on the empirical support for their different beliefs. But to determine the nature of their (dis)agreement, people need to state their beliefs in terms clear enough to display their differing opinions (Wittgenstein, 1922).
This distinction is not mere hair-splitting, for it concerns the interpretation of latent variable modeling of survey data (Bagozzi, 2011; Borsboom, 2008). In surveys, people are asked about their attitudes or opinions—“psychological facts,” in Russell’s terminology. The ensuing data are taken as measures of “empirical facts,” used to test social scientific hypotheses about how such empirical facts are related (Shadish, Cook, & Campbell, 2002). If the detected patterns can be shown to be created by semantics (i.e., the mutual relationships of meaning in the items), the data are probably not measuring the purported “empirical” domain, but instead, what is represented are the semantic relationships (or the “logical relationships,” in Russell’s and Wittgenstein’s vocabulary).
In light of modern psychology, we need to make an adjustment to Russell’s and Wittgenstein’s terminology. Strictly speaking, the “logical” relationships may also be regarded as the workings of psychological mechanisms, but these are of a fundamentally different kind than attitudes. The ability to read and recognize meaning in verbal statements is also a psychological process, but it is created by the language-parsing mechanisms in the cerebral cortex (Jackson, Hoffman, Pobric, & Ralph, 2016; LaPointe, 2013; van Berkum, Koornneef, Otten, & Neuwland, 2007).
The capacity of the cerebral cortex for processing semantic structures in language is central to logical reasoning, but does not in itself process attitudes or truth values of statements. This is necessary for our ability to assess statements with which we do not agree or even products of mere fantasy. The assessment of attitudes and agreement are linked to a broader range of cerebral structures including sub-cortical emotional processing (de Vries, Byrne, & Kehoe, 2015; Fisher, Island, Rich, Marchalik, & Brown, 2015; Honey, Thomson, Lerner, & Hasson, 2012; Nakagawa, Takahashi, Okada, Matsushima, & Matsuda, 2015; Regev, Honey, & Hasson, 2013). For analytical reasons, it is important to keep these two domains apart, and so in the following we will keep the distinction between the three types of facts: Empirical facts established by scientific observation, psychological facts concerning what subjects believe, and logical facts that are simply constituted by coherent and meaningful propositions unrelated to their truth or credibility.
The core element in our method is to use natural language parsing algorithms to compute estimates of how the meaning of survey items overlap. We are using two types of algorithms, one called latent semantic analysis (LSA; Landauer, 2007) and another termed MI after its inventor (Mihalcea, Corley, & Strapparava, 2006; Mohler & Mihalcea, 2009). The nature of these will be more closely described in the methods section below. The output of these algorithms is structurally similar to the correlation matrix for the survey variables, but the numbers do not in any way represent attitude strength. Instead, they are simply estimates of the degree to which the items contain similar propositions. We call the output “semantic similarity indices” and they are similar to what we described as “logical facts” above, in that they only represent the cognitive similarity of statements.
To achieve the aim of this study, we must find a way to differentiate the influence of item semantics from attitude strength in individual survey response patterns. We do this by computing two different response matrices for each respondent—one that is sensitive to response strength, and one that is insensitive to response strength but closer to mere semantic influence.
The rationale behind these two types of matrices starts with how the Pearson product-moment correlation formula picks up the individuals’ contributions, as this is the central condition for what happens in further steps of the analysis. The individual contribution in this formula consists of multiplying two variables x and y for every participant, thus the name “product-moment,” and preserves the magnitude of the variables in each subject. The other elements in the formula simply serve to standardize the variables and centralize the scale around zero. In principle, a matrix of correlations for a sample consists of the average, normalized values of x multiplied by y.
If we multiply each response with all other responses on an individual level, we have for each person what we call an individual co-product matrix. It is structurally similar to the sample correlation matrix, but contains no information about other people’s responses—nothing about the sample variation. It should hence preserve information about the respondents’ attitude strength. For example, a person scoring 4 and 5 on x and y will obtain a co-product of 20, but the co-product for a person scoring 1 and 2 will only be 2.
We can compute another, but similar matrix for each person that is relatively decoupled from the individual’s attitude strength. By subtracting the score on each variable from every other variable and keeping the absolute difference, we obtain what we call an individual item distance matrix. Again, it is structurally similar to the sample correlation matrix, displaying a numerical value for each combination of variables. This matrix contains little or no information about the subject’s attitude strength. To repeat the example above, the item distances for a person scoring 4 and 5 will be 1, but the distance score for a person scoring 2 and 1 will also be 1.
The individual item distance matrix is theoretically akin to the semantic similarity matrix because of two conditions regarding the distances: (A) Any two items containing the same proposition should logically be rated in the same way regardless of the subjects’ endorsements of the items. (B) Conversely, for two items to have different scores, the respondents would need to perceive them as different. So, although there may be other reasons why items are scored similarly, these two conditions together should make the item distance matrix converge around how similarly any subject perceives these items, regardless of the subject’s attitude strength. In contrast, the same individual’s co-product matrix would express similar information, but with the added information of the individual’s attitude strength.
The purpose of these two matrices is to compare how similar the responses of each individual are to our two criteria: the observed sample correlation matrix and the semantic similarity matrix. We may then proceed to explore the relative impact of semantics and attitude strength for each subject, and for each sample in our study.
Since it may be hard for the reader to keep track of the different types of matrices, we have created a sample for comparison in Table 1. It displays the statistics for a survey scale with six items measuring intrinsic motivation, originally published by Kuvaas (2006b). The wordings of these items are:
The tasks that I do at work are themselves representing a driving power in my job.
The tasks that I do at work are enjoyable.
My job is meaningful.
My job is very exciting.
My job is so interesting that it is a motivation in itself.
Sometimes I become so inspired by my job that I almost forget everything else around me.
In Table 1, the correlations among these items in the sample from our second dataset (N = 255) are displayed on the top left. The matrix on the top right displays the semantic similarity indices (MI values) for the same items. On the bottom, we have displayed the item distance matrix (left) and the co-product matrix (right) for a randomly selected respondent in this sample, who scored 5, 5, 4, 5, 5, and 4 on these six items.
The two different computations may seem a bit confusing at first, so a quick recapitulation and comparison may be helpful. The main purpose is to explore how individual response patterns are informed by semantics, and how this influence contributes to the sample statistics. The co-product procedure of multiplying all items with all other items was chosen for two main reasons: First, because we will use the sample correlation matrix as a criterion for our further analyses (this, or its closely related derivative the covariance matrix, being the point of departure for much psychometric modeling). The co-product is the individual value that comes closest to the individual’s contribution to the sample correlation matrix. Hence, the co-product should ideally be the values informing the correlation matrix. Second, a frequent assumption in quantitative models is that factors interact to create their effects. As an example, the “interaction term” in multiple regression is usually entered as a multiplication of the interaction variables (Aiken, West, & Reno, 1991). On the basis of these arguments and traditional practice, the co-products are the most obvious candidate for examining the individual’s contribution to sample data patterns based on measurements of attitude strength.
On the contrary, the item differences that come from subtracting the item scores from each other are practically devoid of information about attitude strength. Although one may object that difference between the scores 4 and 3 depend on attitude strength, the difference is the same as between 4 and 5 or 2 and 1. From the point of view of attitude measurement, the distances take the “quanta” out of the numbers, as can be seen in Table 1.
The strength of attitudes is important because it could conceivably signal a propensity for action if the attitude strength reaches a certain level, which has been a core problem in attitude research since the 1930s (Fishbein & Ajzen, 1975; Kim, Hahn, & Lee, 2015; LaPiere, 1934; Likert, 1932; Prinz, Aschersleben, & Koch, 2009; Triandis, 1980; Zimbardo, Ebbesen, & Maslach, 1977). If the recordings of attitude strength are only used to compare similarity of responses, the information about attitude strength is left out of the picture. The item distances represent information about the similarity between responses without considering the absolute level of these responses. Seen as item distances, the Likert scale numbers simply provide a medium for expressing proximity in meaning.
A main proposition of this study is that we can separate attitude strength from semantic processing in individual records by computing these two matrices for each respondent. We can explore if the compliance with semantic structures is related to attitude strength, or if this information is simply a product of response proximities. We can do this by exploring their relationships to the two criteria: the semantic similarity matrix, which we know is unrelated to attitudes (because it is created by a computer using the text alone), and the sample correlation matrix, which is a result of respondents expressing their attitudes.
The sample correlation matrix commonly serves as the input for further modeling, together with its derived relative the covariance matrix (Abdi, 2003; Fornell & Larcker, 1981; Jöreskog, 1993; Jöreskog & Sörbom, 1993; Marsh et al., 2010; Podsakoff, MacKenzie, & Podsakoff, 2012). To the extent that this data structure contains information about attitude strength, it should be statistically more strongly related to the individual subjects’ co-product matrices. Conversely, the item distance matrices should be more strongly related to the semantic values matrix. The relative influence of semantics on each subject would then be the degree to which the response patterns of individuals are more closely resembling the semantic patterns than the sample correlation matrix.
The sample correlation matrix and the semantic values matrix are used here and referred to as “criteria” because of the following conditions: If a single respondent’s matrix is structurally similar to the sample correlation matrix, then this person is simply responding in a statistically average way—the pattern that emerges is characteristic of the whole sample. With varying departures from this pattern, the respondent is responding in a way that differs from the statistically common pattern. Conversely, if a person’s matrix is similar to the semantic values matrix, he or she is in accordance with what is semantically expected. We can therefore explore at least three characteristics of individual responses: (1) the degree to which their responses are congruent with what is semantically given, (2) the degree to which patterns in their attitude strength is similar to what is semantically given, and (3) which aspect of their response pattern—attitude strength or semantic congruence—is more likely to be contributing to the final statistics for the whole sample.
The various matrices can be compared in terms of the relationships visualized in Fig. 1. The sample correlation matrix (upper left triangle) includes the empirically obtained numbers from the whole sample. The semantic matrix (upper right triangle) has the same structure of items, but their relationships are only computed by semantic algorithms, and no responses are involved. The two individual matrices (lower central triangles) exemplify the same structures for individuals, obtained in the form of either a co-product matrix (bottom left) or an item distance matrix (center right).
STSR and linguistic algorithms
We have assessed the semantic properties of the items using several available algorithms, primarily focused around LSA and WordNet-based approaches (e.g., Dennis, Landauer, Kintsch, & Quesada, 2003; Landauer, 2007; Larsen & Monarchi, 2004; Larsen, Nevo, & Rich, 2008; Li, McLean, Bandar, O’Shea, & Crockett, 2006; Mihalcea et al., 2006). They share the commonality of only analyzing pure text (i.e., no data about how respondents may endorse propositions in these texts).
Text algorithms are a complex topic and a detailed presentation of the procedures involved is not possible within the present format, so we will only describe them on a superficial level below. For more details, we must refer to the appendix of Arnulf et al. (2014) or more technical sources, such as Dennis, Landauer, Kintsch, and Quesada (2013) for LSA or Mihalcea et al. A quick and user-friendly introduction can be found at lsa.colorado.edu for LSA. An approach more suitable for analyses like the present study can be found at http://sims.theorizeit.org/.
When comparing individual responses to semantics, we use only a single text algorithm termed MI, originally developed by Mihalcea et al. (2006; Mohler & Mihalcea, 2009). We do this to avoid complexities in establishing a joint semantic matrix with values from several types of algorithms. From the previous studies, the MI values seem to be the single most powerful predictor of the responses (Arnulf & Larsen, 2015; Arnulf et al., 2014). MI is particularly well-suited for short sentences and derives its information about the meaning of words from a semantic knowledge base and term ontology called WordNet (Miller, 1995; Poli, Healy, & Kameas, 2010). In WordNet, words are organized into a hierarchical structure (an upside-down tree) with synsets (groups) of synonymous words throughout the tree. The further down in the tree a word occurs, the more specific it is, so two words that are part of the same “branch” but at different depths have different specificity (e.g., pear –> edible fruit –> produce). Words may be at the same depth in the hierarchy but in different branches. For example, the words car and pear may be similar in that they are as far down in their branches as WordNet will go (Asian Pears and BMW models are not included). WordNet allows word similarity to be computed by measuring the path length and path depth between two words in the database. MI’s word specificity juxtaposes subtle nuances of meaning (e.g., apple and pear) and generic conceptual meaning (e.g., fruit and vegetable). WordNet is a general lexical database, and MI therefore reflects neutral, “everyday” language and lacks domain-specific knowledge.
The MI algorithm first identifies single words in each sentence and computes similarity as the shortest distance between these words’ synsets (sets of synonymous words) in WordNet (Mihalcea et al., 2006; Mohler & Mihalcea, 2009). Word similarity scores are taken as inputs for a formula on sentence-level similarity. Thus, MI is built first on word-level meaning, moving up to sentence-level structures embedding the words. The output of MI is a similarity score between 0 and 1, where 0 indicates no semantic overlap and 1 indicates an exact match. In the following, these numbers will be referred to as “semantic similarity indices.”
Semantic similarity indices are then computed through the MI algorithm as the semantic distance between any pair of items (Item 1–Item 2), (Item 1–Item 3), and so forth. The resulting output is a matrix representing the semantic relationships across all items. The following two items may serve as examples: “Generally, I like to work here,” and “I would be very happy to spend the rest of my career with this organization.” In our surveyed data, these are found to have a correlation of .51, and their MI similarity index is .50 (a magnitude equivalent to their correlation).Footnote 1
However, when estimating the influence of semantics on the whole sample, we can use multiple regression to complete the MI values with the values from LSA used in previous analyses (Arnulf et al., 2014). LSA is different from MI in that it “demonstrates a computational method by which a major component of language learning and use can be achieved” (Landauer, 2007, p. 31). The way LSA extracts “meaning” from sentences is by relying on huge volumes of text fragments organized along a specified number of dimensions (a usual number of dimensions is 300). The multidimensionally represented texts are called “semantics spaces” in which all terms have specific locations, represented as vectors. New combinations of words can be mapped as vectors in these spaces, resulting in quantitative measures of their similarity with other expressions. For this reason, LSA has by some of its pioneers been argued as a mathematically based theory of meaning (Deerwester, Dumais, Furnas, Landauer, & Harshman, 1990; Landauer, 2007). It is possible for LSA to determine that two sentences share the same meaning even if they do not share words or appear in the same passage. The reason for this is that the aggregated patterns of the semantic spaces will indicate the intended meaning of a sentence relative to all other possibilities in the semantic space.
Comparing two texts “Doctors operate on patients” with “physicians do surgery,” LSA returns a cosine of .80. Comparing “The radius of spheres” with “a circle’s diameter” the cosine returns .55, but between “The radius of spheres” and “the music of spheres,” the cosine is as weak as .01 (Dennis et al., 2003). Because these methods have been presented in detail elsewhere (Arnulf et al., 2014; Gefen & Larsen, 2017; Larsen & Bong, 2016; Nimon et al., 2015), we refrain from elaborating on LSA here. The main point is that each of these algorithms have limitations so that a bundle of MI values and LSA extracted cosines performs better in predicting human language parsing than each of them in isolation.
Attitude strength or semantics—Does it matter?
At first glance, one may ask whether the difference between semantics and attitude strength matters in practice, here operationalized as item distances and co-products. Many researchers are used to constructing measurement scales with different wordings of the same items. This is a frequent way to ensure that the scale taps different facets of a construct while keeping it internally consistent and delimited from other measures included in the instrument (Nunnally & Bernstein, 2010). So far, the semantic similarities would be expected.
The real problem, however, appears if the other constructs tested are similarly determined by the semantic relationships, such that there is a necessary semantic relationship between the independent and dependent variables. In that case, the “factors” are not separate, but still only facets of the same phenomenon. To prevent this, researchers commonly apply various techniques such as factor analysis to ensure the relative independence of these measures (Abdi, 2003).
The theoretical insufficiency of this assumption was poignantly outlined by van Knippenberg and Sitkin (2013), who showed that the construct of “transformational leadership” conflates the independent with the dependent variable through definitions and operationalizations. Empirically, the tautological link between leadership and other constructs was demonstrated in the first article on STSR (Arnulf et al., 2014), where the relationship between all constructs was found to be determined by semantics, notwithstanding the rotated factor structures.
If research models simply end up with “what can be said,” this may explain why inflated statistics and a lack of predictive validity often result from such models (Bagozzi, 2011; Gollwitzer & Sheeran, 2006; Podsakoff, MacKenzie, & Podsakoff, 2012; Podsakoff & Organ, 1986). From a research point of view, it may actually be more interesting to see if attitude strength may override cognitive restraints on behavior. Theories on organizational behavior frequently hypothesize that affective responses to leaders, job characteristics and social environments reduce calculative behaviors (e.g., Conger & Kanungo, 1998; Felfe & Schyns, 2014; Ilies, Nahrgang, & Morgeson, 2007; Kuvaas, Arnulf, & Dysvik, 2008). For research to make progress in this field, it is important that methods distinguish between the cognitive, semantic relationships between words describing workplaces and the affective or attitudinal dynamics that shape loyalty, commitment or their negative counterparts.
The problem of signs
MI values do not take negative values at all, and when LSA cosines are negative, it does not signal a contrary statement. Thus, the algorithms cannot detect that an item is reversed, as is sometimes the case in surveys. Some survey structures depend heavily on negative relationships and so finding a way to deal with this is important to estimate the actual relationship between the semantic and the surveyed matrices.
In this study, we follow the same procedure described previously by Arnulf et al. (2014), simply correcting the sign of the semantic values for reverse-scored items. One special case is the Multifactor Leadership Questionnaire (Avolio, Bass, & Jung, 1995), which does not contain reversed items. Instead, about one fourth of the 990 item pairs were negatively correlated because their subscales are theoretically devised to be the opposite of effective leadership (“laissez-faire” and “passive management by exception”). As we have described elsewhere (Arnulf et al., 2014), their negative relationships can be argued a priori, similarly to using one-tailed instead of two-tailed significance tests. We tested this argument by making signs of semantic identity negative when items combine positive leadership with the subscales “laissez-faire” and “passive management by exception” and thereby correctly identified 255 of the 264 negative correlations (p < .001).
Samples and measures
We compared individual response patterns from the following four datasets, establishing a sample correlation matrix and a semantic similarity matrix for each dataset. For each respondent in each sample, we computed their respective co-product and item distance matrices.
A sample of 1,220 respondents filled out the Multifactor Leadership Questionnaire (MLQ) (Avolio et al., 1995) rating their immediate superior manager. The original sample consisted of 1,649 persons from a Norwegian bank who responded to a Norwegian translation of the survey. In the present analysis, we only included respondents for whom the demographics were known. Overall, 48.9% were females, the sample age mean was 46 years, 71% were not managers, middle managers made up 26% and 2% listed themselves as top managers. The MLQ contains 45 items, yielding a matrix of 990 unique pairs of items.
This contains responses from 255 scientists and engineers in a governmental research agency. They responded to the MLQ (Avolio et al., 1995) rating their own superior managers, but in addition responded to scales measuring perceptions of economic and social exchange (seven and eight items each; Shore, Tetrick, Lynch, & Barksdale, 2006), six items measuring intrinsic motivation (Kuvaas, 2006b), seven items measuring organizational citizenship behavior (OCB; van Dyne & LePine, 1998), five items measuring turnover intention (TI; Kuvaas, 2006a), as well as ten items measuring work quality and work effort (Kuvaas, 2006b). In total, the survey contained 79 items producing 3,081 unique pairs in each of the matrices. Demographics revealed 66.7% were male with a mean age of 38 years.
In this sample, 981 employees from the Norwegian Armed Forces responded to a broad range of diverse items concerning leadership and other OB variables rating their own superior managers: 20 items from the MLQ (Avolio et al., 1995); eight items measuring leader–member exchange (LMX; Bernerth, Armenakis, Feild, Giles, & Walker, 2007); 20 items from the Leadership Behavior Development Questionnaire (LBDQ; Stogdill, 1963), of which ten items are related to initiation of structure and ten items to consideration. Additionally, eight items were from a scale measuring affective organizational commitment (Meyer, Allen, & Smith, 1993), job satisfaction (three items) (Cammann, Fichman, Jenkins, & Klesh, 1979), TI (Kuvaas, 2006a), and a scale measuring self-rated work quality and work effort, with altogether ten items (Kuvaas, 2006b). In total, the 69 items in this survey provided 2,346 unique pairs of items in the various matrices computed. No demographics were available in this sample.
This consisted of a sample of 5,332 students responding to an officially translated Norwegian version the NEO-FFI, which is a commonly used five-factor personality inventory (Costa & McCrae, 1992; Martinsen, Nordvik, & Østbø, 2003). This is a short form with 60 items, yielding 1,770 unique pairs of correlations in the various matrices. Demographics for the sample showed the mean age to be 25 years, and 44.7% were male.
We computed the co-products and distances matrices for all respondents in all four datasets. This included a total of 7,787 respondents supplying one co-product matrix and one distance matrix each, yielding a total of 27,461,502 observed item pair responses. For each respondent, we explored how similar each of the matrices were to the two criterion matrices, the observed sample correlation matrix and the semantic matrix, respectively. To describe similarity, we simply used the Pearson correlation between the individual’s matrix and the two criteria. If a person’s co-product matrix correlates highly with the correlation matrix (regardless of response strength), this person contributes to the observed pattern in sample statistics (in the form of alphas and factor structures derived from these). On the contrary, if the person’s co-product matrix correlates weakly with the observed sample matrix, this person’s contribution to the sample contains noise that is filtered out in the sample matrix.
We measured the individual’s similarity with the semantic indices in the same way. A person whose individual matrices correlate highly with the semantic similarity matrix can be said to comply with the expected semantic patterns of the survey. In the case of weak correlations, the individual can be said to depart from the semantically expected pattern. As we argued above, we expect the semantic similarity index matrix to be closer to the individuals’ item distance matrices than to their item co-product matrices.
For each individual, we computed these similarities (correlations between their individual matrices and the two criteria) and retained these for further explorations. We also averaged the co-products and differences across individuals and obtained another two measures: The average item distance matrices and the average co-products for each of the four samples.
The literature on partialing independent variables sometimes suggests that such comparisons should be done using intraclass coefficients (Lynam, Hoyle, & Newman, 2006). However, in this case we chose to stay with the simplest procedures possible. The sources we compare are identical constructs (the contents of the scales) and the only differences that we compare are between the calculations of co-products and distances. We are simply exploring which aspects of the individual response patterns are most similar to the observed sample statistics. In no case did we try to nest analyses as these procedures have not been tried before, and we want to reduce complexities until a solid methodology is established in the field of survey semantics.
Table 2 shows the distributions for co-product and distance similarities. Although the values vary, the relationships are strong for the first three datasets containing OB surveys, but they break down in the case of the NEO. The differences among all the means are statistically significant, with the following exceptions: In Samples 1 and 2, the co-product matrices’ similarities with the sample matrix are nonsignificantly different from the distance matrices’ similarity with the semantics. In Samples 3 and 4, there is a nonsignificant difference between the co-product and difference matrices in their similarity with semantics.
Generally, there does not seem to be much difference between the distance and co-product matrices in terms of their distributions. The distance matrices seem to reach higher maximum similarities with the observed correlation matrix as well as with the semantic values, and their minimum values are also not as low. The latter phenomenon may be due to the fact that an individual’s co-product matrices can be negatively related to the sample correlation matrix.
Figures 2, 3, 4 and 5 show the distributions of two individual-level variables: How similar the individual co-products are to the correlation matrix (sorted in this order), and the item distance matrix similarity with semantics for the same individuals:
The plots show that for the first three datasets, to the extent that the individual’s co-products are similar to the observed correlation matrix, the same person’s item distance matrix will be similar to the semantic values. In the fourth dataset, containing the NEO data, this phenomenon is not obviously present. Also, in the first three datasets, an extreme negative relationship between the co-product matrix and the sample correlation matrix implies higher compliance with what is semantically expected. This suggests that in the individual responses, there is a relationship between response strength and the sample correlation matrix.
We therefore turn to an exploration of how the individuals’ score levels (indicating attitude strength) relate to how similar the individuals’ co-product and distance matrices are to the two criteria: sample correlations and semantics. Table 3 displays the data for all four datasets.
The findings in Table 3 show that attitude strength (score levels) are more strongly related to the co-products than to the item distance matrices. This is expected theoretically, both because measuring attitude strength is the purpose of the surveys and because of the correlation coefficient formula. However, for the first three datasets, the scale levels are not only related to how similar the co-products are to the correlation matrix—they are also related to how the co-products relate to the semantics. It is as if people who respond strongly to the theoretically favorable conditions in the OB surveys are also more compliant with the semantic patterns, possibly because they pay more attention to the exact wording of the survey. Conversely, people expressing more moderate attitude strengths are responding with less compliance to the semantically expected patterns.
This relationship is much weaker for the NEO data, and Table 3 also holds more differential information about possible explanations. It turns out that the personality scores are differently sensitive to semantic values. Table 4 shows that the five traits have very different impacts on an individual’s response patterns—both in the way they relate to the sample matrix and in the extent to which they are influenced by semantics. Not surprisingly, people scoring high on conscientiousness are compliant with semantics, as are people who score low on openness. These individuals may be more inclined to interpret the text in literal terms, and hence be more semantically predictable. People who score low on neuroticism display a strong tendency to respond very differently from all other people—their responses are negatively predicted by the sample correlation matrix.
One reason why neuroticism correlates so highly with semantics in Table 4 is that it may be due to noise. If many of these individuals respond differently from others, they probably also respond differently from each other. It is possible that the only thing such people have in common is the semantic properties of these items, thus strengthening the relationship between semantic compliance and neuroticism. This is illustrated as a plot in Fig. 6. Figure 7 shows that the personality trait conscientiousness has the opposite relationship to the sample matrix.
Dataset 4 is therefore particularly valuable in showing that people need not respond in ways that are semantically determined. Compliance with what is semantically expected seems to depend on a number of conditions, including attitude strength and personality traits.
Dataset 1 originally contained a shortened version of the NEO that was not included in the previously published study by Arnulf et al. (2014). Including information about personality in the present analysis allows us to check how demographics and personality may affect semantic compliance in the MLQ data, which is usually where semantics show the strongest influence. We regressed the similarity of the co-product and distance matrices with either the sample correlations or semantics, on demographics, NEO scores, the MLQ scale values, and finally the respondents’ management level. The results can be seen in Table 5. It appears that demographics are not important, but personality and respondents’ satisfaction with their own manager play roles for all matrices.
It can thus be demonstrated that the co-product matrices capture diverse sources of variance influencing individuals’ responses, such as their attitude strength, personality dispositions, and management level. All of these variables seem to influence the attitude strength of individuals, as well as their coherence with expected semantic properties of the scale.
But how much of this individual-level information is carried over into the sample characteristics? To explore this, we averaged the item co-products and item distances across respondents for each pair of items in all datasets. This level of analysis corresponds to the second step in the formulas for correlations or covariances, in which the sums of products are divided by sample size. Table 6 displays the relationships between the sample correlation matrix, the semantic matrix, and the averaged co-products and distance matrices for all four samples. For all samples, the average-distance matrix is more closely related to both the sample correlation matrix and the semantic matrix. Interestingly, in the first three datasets, the sample correlation matrix is also more strongly correlated with the semantic values than with any data generated by respondents (co-products or distances).
In Tables 7, 8, and 10, the sections display the following analyses: Tables 7 and 8 explore the degree to which the co-products (Table 7) or distances (Table 8) are explained by semantics. As we argued initially, for Datasets 1–3, the item distance matrices are much closer to the semantic values than to the co-products.
In Table 9, we use hierarchical regression to explore the degree to which the observed sample correlation matrix is differentially explained by semantics, co-products, or distances. We entered the semantic values in Step 1. It appears that the co-products have a minute impact on the observed sample correlations, since only the distance matrix scores improve the models in Step 2. This also holds for Dataset 4, the NEO scores.
Finally, as is displayed in Table 10, we regressed the average co-product and distance matrices on the semantic values, keeping the residuals, using these as estimates of scores after controlling for semantics. We then used hierarchical regression to predict the sample correlation matrices. Entering the residuals of the co-products in Step 1, these still had predictive power until the residuals of the distance scores were entered in Step 2. Here again, the co-products lost most of their predictive power, becoming nonsignificant in one case, and of minute practical importance in the other cases.
In this way, it appears that although the co-products carry substantial amounts of information about individuals’ response patterns (and their sources of variance), this information is largely lost in the average sample matrices. What appears instead is a function of the item distances, which are mainly informed by semantics.
This study has served two purposes: Primarily, we sought to develop a method for assessing how cognitive processes in the form of semantic structures influence individual survey respondents. Also, we wanted to show how the commonly applied statistical techniques departing from correlation or covariance matrices run a real risk of filtering out attitude strength, its own subject matter, to instead reflect the cognitive language parsing mechanisms of the respondents.
Since no previously validated method exists to answer this question, we have argued that individual-level analyses can be performed by calculating two different types of individual-level response matrices: the co-product and item distance matrices. Departing from the formula for product-moment correlation coefficients, we argue that by multiplying the paired responses for all individuals, the co-products should capture the response strength. Conversely, individual matrices computed as absolute distances (subtracting response X from response Y) should be relatively distinct from attitude strength and closer to the expected semantic values.
Our analysis seems to support these assumptions. Although the two kinds of matrices contain much of the same information and display similar distributions, the individual co-product matrices are most sensitive to the respondents’ scale score levels, indicating their attitude strength. The distance matrices seem less sensitive to score level (attitude strength) and are more strongly related to the semantic properties of the scales.
The exploration of the individual co-product matrices shows that these contain rich information about a number of respondent characteristics. Among the sources of variation found were personality, satisfaction with one’s own manager, and personal management level. In the case of the NEO-FFI, the personality trait levels exerted a much stronger influence on the individual response patterns than did the semantic properties of the items, in line with previous findings (Arnulf et al., 2014). However, when aggregated on sample levels, the explanatory power of the distance matrices dominated completely, and almost nothing was left of the information from attitude strength. This was even true in the case of NEO-FFI scores, but in this case, the distances were still only weakly informed by the semantic properties of the items.
To understand how and why this happens, the NEO matrices were informative. The aggregated correlation matrix for the whole sample displayed a structure that most individuals do not display themselves. Even the mean co-product matrix for all respondents does not reach a higher similarity than a correlation of .21 with the matrix for the whole sample, and no individual had a correlation higher than .45 with the sample structure. This means that for each individual, there is considerable variation in the ways that response patterns emerge, and no one displays an entirely “normal” response structure in the statistical sense. This can be assumed to contribute to the predictive validity of the Big Five in many areas (van der Linden, te Nijenhuis, & Bakker, 2010) because individual response patterns are allowed to be widely different from the norm, hence capturing more idiosyncratic patterns characterizing the individuals. Responses to the items in NEO-FFI may reflect stable behavioral dispositions that are pervasive in the respondents’ autobiographic memory. Hypothetically, personality may be a part of how the respondents apply their cognitive semantic processes, hence reflecting more “fundamental” psychological processes than those normally applied when answering surveys.
This is not so for the OB scales in the three other datasets, in which the similarity is much higher. The mean correlation is around .45 and the maximum values as high as .90. This distribution may even have been a goal for the scholars developing the scales, since this will greatly enhance the alpha reliability, factor structure, and model fit indices of the scales, which are taken by many journals as quality criteria (Abdi, 2003; Arnulf et al., 2014; Fabrigar, Wegener, MacCallum, & Strahan, 1999; Nunnally & Bernstein, 2010). Failing to comply with such criteria has even been raised as an objection against the five-factor model (McKenzie, 1998).
When item semantics become the main common factor shaping the responses to the survey, it implies either that the respondents have little else in common, or that the survey elicits few other types of responses. In the NEO sample, Neuroticism seemed to make people answer in dissimilar ways that left little other than semantics in common. It also appears as if conscientiousness increases the effort to comply with the requirements of the survey, and low values of openness to experience seemed to create a propensity to answer the survey items in very literal ways, akin to the stale patterns detected by the computerized semantic algorithms.
The key to understanding the influence of semantics in surveys may reside in the well-known tenet of classical psychometrics, that all sources of variance in responses will be filtered out as noise if they are randomly distributed (Nunnally & Bernstein, 2010). In our study, this seems to happen with many sources of variation that determine attitude strength in surveys on OB. Even if attitude strength appears to be an important determinant of individual co-product matrices, reflecting meaningful differences among the respondents, the effects of attitude strength seem to disappear in the averaged sample matrices. What is left is the common denominator of most respondents—their compliance with the semantic criteria in the items.
It is compelling that the observed sample matrices, themselves computed by adding the co-products of items, seem to lose their roots in these values. The co-products should have emerged as important if only due to common method bias since these were the input values for the correlation matrix (Podsakoff et al., 2012). When the matrix of average distances emerges as the most powerful predictor of the observed correlation matrix, it can only be explained by reducing the role of attitude strength to a mere carrier of semantic information.
These findings are troublesome for the interpretation of factor analyses and latent factor modeling on a theoretical level. Correlation as a method has always been known as being vulnerable to the problem of the “third variable” in whatever form (Antonakis, Bendahan, Jacquart, & Lalive, 2010). The present study suggests that the relationships picked up in correlation matrices may not even be due to extraneous factors influencing relationships. As was recently shown by Maul (2017), data structures with good psychometric properties can be obtained not only with nonsensical, but even with empty items that cannot possibly reflect any attitude strength whatsoever. From the semantic perspective in our case, it appears that the method of correlating Likert-scale data may easily become detached from its own subject matter—the attitude strength—and instead pick up patterns created by the cognitive process of linguistic parsing when reading the items. Such a situation is clearly in conflict with Likert’s original viewpoints on the value of his method (Likert, 1932), and shows how Thurstone was right in his doubts about the numbers collected by Likert’s scales (Andrich, 1996).
When this happens, the method has lost its purported object and the findings are no longer concerned with the attitudes toward the contents of the survey. When factor structures and other model characteristics of survey data are based on semantics, they are no longer empirical, but semantic, similar to what Russell and Wittgenstein thought of as “logical” facts (Russell, 1922).
We believe that the reason for these important differences between the OB scales and the NEO personality items may be found in a subtle difference in the construction of items and scales. Psychometric techniques originate from intelligence testing (Likert, 1932, p. 50), where the focus of interest was actual behaviors (e.g., response time or error rate) and not the endorsement of propositions. The items in personality tests such as the NEO sample from observations of earlier behaviors—for example, work habits, episodes of self-control, and aesthetic experiences. Although the personality test items may superficially look similar to the OB counterparts, they are actually sampling a wide range of behavior frequencies. To the extent that respondents report overt and quantifiable behaviors, the information is non-semantic. Some authors argue that test items should include broad samples of behavior instead of seeking high alpha reliabilities through similarly worded items (Kline, 2000). This approach probably creates messier factor structures and alphas, but it does seem to cluster non-semantic relationships between behaviors in peoples’ lives.
The OB items are much closer to Likert’s original view of his instruments as “dispositions toward overt action” or an “indirect method” (Likert, 1932 p. 9). Following Likert’s work, measures of attitudes have been asking the respondents to rate opinions on anything from US-Japanese relations (Likert, 1932) to ease of use in computer software (Davis, 1989). Such questions rarely tap information about observed behaviors, but are much more likely to address purely cognitive constructions (Gefen & Larsen, 2017). As was shown by Gollwitzer and Sheeran (2006), attitudinal measures can only modestly predict behavior unless the subject has previous observations of own behavior. Researchers may infuse instruments with semantic relationships that will raise alpha reliabilities, but this will not necessarily improve the predictive validity of the measures.
The application of statistical methods to the purported measurements of latent, but verbally defined constructs is mathematically complex and fraught with unsolved questions about quantification (Slaney, 2017). To the degree that items tap information about more or less overt behaviors, their quantification may be more straightforward than measurements of attitudes. We are currently working on designs to explore the relationships between semantics and behavioral assessments in more detail. On the other hand, we think this opens up a fascinating new perspective on Likert scales as a psychological method. If the semantic influence on survey responses has been both pervasive and neglected for decades, it means that the language parsing mechanisms of the brain have been taken almost for granted. The capability of a fluent reader to parse and understand language is usually quite effortless (Kahneman, 2011), and at the same time remarkably precise in its ability to recognize minute differences between short items in surveys (Michell, 1994). An improved theory of cognitive processes involved in survey responses—STSR—offers at least two interesting further paths.
First, the cognitive structure needs to be consistent across subjects, because this is a prerequisite to hold different opinions about the same subject matter (Coombs & Kao, 1960; Russell, 1922). It would be interesting to establish a method to describe the common cognitive model that respondents need to share in order to respond in reliably different ways. The common ways of using Likert-scale data until now has largely been to find statistically significant patterns using null hypothesis significance testing (Krueger, 2001). This may be one of the reasons why models based on survey data suffer from common method variance and poor predictive validity (Bagozzi, 2011; McClelland, Koestner, & Weinberger, 1989; Podsakoff et al., 2012). If we had a way of establishing an expected semantic pattern of responses, it may serve as a better platform for testing nonobvious behavioral relationships than simply rejecting a null hypothesis (Arnulf, Larsen, Martinsen, & Bong, 2015; Rodgers, 2010; Smedslund, 1994).
Secondly, and conjunctive to this, it may be much more interesting and informative to explore how survey data deviate from the semantically expected. Our capacity for abstract thinking seems to originate from the brain’s spatial capabilities, and these spatial representations are always distorted (Tversky, 1993). It is conceivable that individual idiosyncrasies may distort the semantic spaces of individuals also, and that these differences are valuable psychological information. The findings of the present study show that respondents leave multiple types of information in their response patterns. If this information is reduced to the semantic commonalities of the participants, we may miss the true value of the collected information. A better understanding of the semantic structures and how they are bent by respondents may offer new insights with better predictive validity because they are closer to the characteristics of the respondents.
Two examples may be useful here: The semantic algorithms predict that transformational leadership will be linked to intrinsic motivation and work outcomes simply because the items have overlapping meanings. A person who endorses his boss (transformational leadership) and likes his tasks (intrinsically motivated) will also not look for a job (turnover intention) because this is simply what these sentences imply. These connections will be discernible in a large sample of people simply because this is how they read the items, on average. It might be more interesting to know whether or how people with strong positive or negative attitudes toward their superiors or jobs also bend their cognitions to fit their world views. So far, we have had no agreements on methods to explore such relationships.
Limitations and implications for further research
This is a type of analysis that has never been undertaken before. Thus, we have few or no criteria for assessing the quality of the displayed statistics. Also, the four samples fall into two very distinct groups—although the OB scales seem strongly determined by semantics, this does not seem to be the case for the personality scales. This opens up a possibility that different types of Likert scales may display very different properties with semantics. This selection of data samples may have influenced or biased our findings, but we believe that the present study has opened a path to more direct investigations of this topic.
An important set of limitations come from the semantic algorithms. As anyone who has tried automatic translation tools will know, text algorithms are not perfect. The MI algorithm has no context-specific knowledge, but is more suitable to short texts like survey items. The LSA cosines are conversely dependent on the semantic spaces used and the number of dimensions applied (usually denoted k). We simply do not possess knowledge about how variations in these characteristics shape the statistics we report here.
Furthermore, we have chosen only to analyze data from the most commonly used types of response scales, on which respondents are asked to indicate their attitudes in ways that are later quantified along a dimension. There are many more types of scales (e.g., Brennan, 2010; Michell, 2013; van Schuur, 2003) that are likely to display other relationships with semantics.
Also, none of our analyses considered how responses were nested within surveys, departments or organizations. We are currently preparing multisource–multimethod studies of new datasets to explore the effect of more complex analyses. We therefore call for further research along these lines. It would be interesting to have more incisive studies of the statistics we introduce here. Further exploration of the statistics of individual response patterns and the influence of semantics is necessary to establish a more solid foundation for further empirical analyses.
With the rapidly increasing use of big data and other analytical techniques, the role of surveys is changing (Kern et al., 2014; Kosinski, Bachrach, Kasneci, Van-Gael, & Graepel, 2012; Kosinski, Stillwell, & Graepel, 2013). The study of how computer algorithms can be applied to psychological materials is a promising field for psychological methodology, already applied in practice by a series of technological companies (Markowetz, Blaszkiewicz, Montag, Switala, & Schlaepfer, 2014). Another line of future research would be to explore how these findings generalize to other domains of Likert-scale data. A more nuanced series of findings could help establish a more solid theoretical foundation for the STSR.
Our final goal would be the establishment of a general model for the semantic processes involved in survey responses. Attempts at this or calls for such endeavors have been published intermittently over the years (Feldman & Lynch, 1988; Michell, 1994, 2013; Schwarz, 1999). With the increasing capability of digital tools (Landauer, 2007; Larsen & Bong, 2016) and neurobiological methods in mapping semantic understanding (Honey et al., 2012), the time seems ripe for a better understanding of the actual psychological processes that end up in the form of scores on Likert scales.
It should be noted that we do not generally expect MI similarity indices to be interchangeable with correlations, but that insofar as semantics have influenced the correlation matrix, there should be a measurable relationship between the two.
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We thank the U.S. National Science Foundation for research support under Grant NSF 0965338, and the National Institutes of Health through Colorado Clinical & Translational Sciences Institute for research support under Grant NIH/CTSI 5 UL1 RR025780.
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Arnulf, J.K., Larsen, K.R., Martinsen, Ø.L. et al. The failing measurement of attitudes: How semantic determinants of individual survey responses come to replace measures of attitude strength. Behav Res 50, 2345–2365 (2018). https://doi.org/10.3758/s13428-017-0999-y
- Semantic analysis
- Survey response
- Semantic theory of survey response (STSR)
- Attitude strength