Consumers’ estimation of calorie content at fast food restaurants: cross sectional observational study2013; 346 doi: http://dx.doi.org/10.1136/bmj.f2907 (Published 23 May 2013) Cite this as: 2013;346:f2907
- Jason P Block, assistant professor1,
- Suzanne K Condon, director2,
- Ken Kleinman, associate professor1,
- Jewel Mullen, commissioner3,
- Stephanie Linakis, project manager1,
- Sheryl Rifas-Shiman, senior analyst1,
- Matthew W Gillman, professor14
- 1Obesity Prevention Program, Department of Population Medicine, Harvard Medical School/Harvard Pilgrim Health Care Institute, 133 Brookline Avenue, Boston, MA 02215, US
- 2Bureau of Environmental Health, Massachusetts Department of Public Health, 250 Washington Street, Boston, MA 02108, US
- 3Connecticut Department of Public Health, 410 Capitol Avenue, Hartford, CT 06134, US
- 4Department of Nutrition, Harvard School of Public Health, 665 Huntington Avenue, Boston, MA 02115, US
- Correspondence to: J P Block
- Accepted 25 April 2013
Objective To investigate estimation of calorie (energy) content of meals from fast food restaurants in adults, adolescents, and school age children.
Design Cross sectional study of repeated visits to fast food restaurant chains.
Setting 89 fast food restaurants in four cities in New England, United States: McDonald’s, Burger King, Subway, Wendy’s, KFC, Dunkin’ Donuts.
Participants 1877 adults and 330 school age children visiting restaurants at dinnertime (evening meal) in 2010 and 2011; 1178 adolescents visiting restaurants after school or at lunchtime in 2010 and 2011.
Main outcome measure Estimated calorie content of purchased meals.
Results Among adults, adolescents, and school age children, the mean actual calorie content of meals was 836 calories (SD 465), 756 calories (SD 455), and 733 calories (SD 359), respectively. A calorie is equivalent to 4.18 kJ. Compared with the actual figures, participants underestimated calorie content by means of 175 calories (95% confidence interval 145 to 205), 259 calories (227 to 291), and 175 calories (108 to 242), respectively. In multivariable linear regression models, underestimation of calorie content increased substantially as the actual meal calorie content increased. Adults and adolescents eating at Subway estimated 20% and 25% lower calorie content than McDonald’s diners (relative change 0.80, 95% confidence interval 0.66 to 0.96; 0.75, 0.57 to 0.99).
Conclusions People eating at fast food restaurants underestimate the calorie content of meals, especially large meals. Education of consumers through calorie menu labeling and other outreach efforts might reduce the large degree of underestimation.
A recent international policy approach to obesity prevention, driven by the growth in consumption of fast food, is to require restaurants to print calorie content on menus. From 2006 to 2010, many states and municipalities in the United States passed laws on provision of calorie content on restaurant menus. These efforts culminated in the federal Patient Protection and Affordable Care Act of 2010, which included a provision that will require all chain restaurants with more than 20 sites in the US to print calorie contents on menus. These policies were driven by the belief that individuals might consume excess calories when they are eating restaurant meals because of limited awareness of the calorie content. Previous research has shown that adults and children underestimate the calorie content of their meals, often by large amounts. These studies, however, were conducted in experimental settings with no monitoring of consumer choices at actual restaurants,1 2 focused on a narrow range of fast food restaurants in samples with limited racial/ethnic diversity,2 3 or were unable to examine differences between age groups or between fast food restaurant chains.4 5
We quantified the difference between estimated and actual calorie content of meals purchased by adults, adolescents, and school age children at six fast food restaurant chains in four cities in New England, US, and assessed the correlates of underestimation.
We interviewed participants dining at fast food chain restaurants in Boston and Springfield, MA; Providence, RI; and Hartford, CT. We considered for inclusion the 10 chains with the highest sales in the US. For adult and school age children samples, surveyed at dinnertime (evening meal), we interviewed diners at the five chains that had at least two sites in each city and catered to dinnertime meals: McDonald’s, Burger King, Wendy’s, KFC, and Subway. For the adolescent sample, collected after the school day or at lunchtime, we interviewed diners at the five chains that had at least two sites within one mile (1.6 km) of a high school in each city. In the Utates, high schools typically include 9th through 12th grades with children aged 14-19; however, some schools include children from broader age groups. These restaurants were the same as for the adult/school age children samples except we omitted KFC and added Dunkin’ Donuts. We excluded pizza restaurant chains (such as Pizza Hut) because of the difficulty in determining the quantity that an individual bought for personal consumption, and we excluded restaurants that cater primarily to adults (such as Starbucks).
At the time of our data collection, none of the chains in our sample routinely printed calorie contents on menus. The chains presented calorie contents, along with additional nutrition information, on wall posters, food containers, napkins, and cups or on limited menus identifying food choices with less than a specified number of calories. All chains presented comprehensive nutritional information on their websites.
Using restaurant locators on chains’ websites, we randomly selected 10 restaurants in each city, stratified by chain, for a total of 40 restaurants for the adult and school age children samples: three McDonald’s, three Burger Kings, two Subways, one KFC, and one Wendy’s in each city. Of the initial 40 restaurants we selected, we excluded one restaurant because it closed in 2011 and four restaurants in 2010 or 2011 because restaurant management refused to allow us to collect data on restaurant premises and no public sidewalk was available from which to work. We replaced these restaurants through either random selection in 2010 or by selecting the nearest restaurant from the same chain in 2011.
We followed the same process for the adolescent sample; however, we selected only from restaurants within one mile of a high school. Again, we randomly selected 10 restaurants in each city, stratified by chain, for a total of 40 restaurants: three McDonald’s, two Burger Kings, two Subways, two Dunkin’ Donuts, and one Wendy’s in each city. Of the initial 40 restaurants, we excluded one restaurant because of management prohibition in 2010, one because of a closure in 2011, and nine because there were no available adolescents to survey on repeated visits in 2010 and 2011. We replaced these restaurants in the same manner as for the adult/school age children sample.
For the adult and school age children samples, we collected surveys together between 5 15 pm and 7 30 pm, from April through August 2010 and 2011. We chose dinnertime (evening) because collection at lunchtime could have restricted the sample primarily to working adults and provided limited opportunity to sample school age children accompanying their parents or legal guardians. We planned six separate visits to each restaurant to sample a broad representation of diners, but on some of the visits, we collected few or no surveys because of limited traffic and non-response. We made additional visits to those restaurants for a total of 269 visits to the 42 restaurants, including the two in 2010 that we had to replace in 2011.
For the adolescent sample, we collected surveys from noon to 2 pm after the start of school summer break in each city, June through August 2010 and 2011. We also collected an after school sample in Boston only, at the same restaurants as for the lunchtime sample, from 2 15 pm to 4 30 pm, April through June 2010 and 2011. Because we targeted adolescents unaccompanied by parents, we chose lunchtime or after school for data collection. We chose restaurants near schools to maximize respondents, assuming summer activities near schools. We anticipated six visits to each restaurant but made additional visits if we collected few or no surveys. Because we visited the Boston restaurants both during the school year and over the summer, we planned 12 visits to each restaurant there. We completed a total of 356 visits to the 47 restaurants, including the seven in 2010 that we had to replace in 2011.
One or two research assistants administered surveys to customers, typically outside the entrance to the restaurants or on a nearby public sidewalk. The research assistants approached all customers who seemed to meet inclusion criteria: those aged ≥18 for the adult sample, those aged 11-20 for the adolescent sample; and those aged 3-15, and accompanied by a parent or legal guardian, for the school age children sample. Children aged 11-15 were eligible for either the adolescent or school age children sample, depending on the time of day. For the adolescent sample, we interviewed the person directly at lunchtime. For the school age children, we interviewed their accompanying parent or legal guardian at dinnertime about the child’s meal. We conducted interviews for the adult and school age children sample during the same restaurant visits, but parents interviewed for the school age children sample were ineligible for the adult sample.
Research assistants approached potential participants as they entered the restaurant and requested their enrollment in a study about “food choices in fast-food restaurants” and asked them to keep their receipt on exit. After collecting the receipt, the research assistants asked each participant to identify which items on the receipt he or she purchased for personal consumption or for their child in the case of the school age children. Additional details on food and beverage choices came from an “item questionnaire” that queried details that were unclear on the receipt, such as whether items were shared, the use of sauces/condiments, the addition of cheese, the type of salad dressing, and specific beverage choices. Research assistants also administered a short questionnaire to gather participants’ open ended estimation of their meal’s calorie content; responses to questions about how important taste, calories, convenience (“quick to eat”), or price was in food choice (“a lot,” “a little,” or “not at all”), and awareness and use of nutritional information in the restaurant (“yes,” “no,” “unsure”); and age, sex, race/ethnicity, height, and weight. Participants self identified race/ethnicity as “white,” “black,” “Hispanic,” “Asian,” and/or “other.” Research assistants further asked participants to estimate their average daily calorie requirement, selected from a list of multiple choice answers. We categorized answers into a wide range of possibly “correct” values of 1000 to 3000 calories, <1000 calories as “incorrectly underestimated,” and >3000 calories as “incorrectly overestimated.” The research assistants interviewed participants in English; questionnaires translated into Spanish were available to guide participants with limited proficiency in English. We gave a $2 (£1.30, €1.50) gift card to each participant for completing the study. We had no explicit exclusion criteria; however, diners who spoke only Spanish could not participate because questionnaires were administered only in English.
Research assistants collected data on 1894 adults, 1180 adolescents, and 333 school age children. We excluded 17 adults, two adolescents, and three school age children (less than 1%) because we did not collect adequate information to calculate the actual calorie content of their meals. Our final sample size was 1877 adults, 1178 adolescents, and 330 school age children.
We counted all potential participants and recorded their sex if they were asked to participate but refused to do so. Among the non-responders we also counted those participants who initially agreed to participate but did not keep their receipt. Of all individuals that we approached, 40% of adults, 42% of adolescents, and 45% of parents with school age children agreed to participate. In each sample the sex ratio of participants (males to females 60:40, 51:49, 53:47) was similar to that of non-participants (57:43, 51:49, 48:52).
As we classified energy content as calories this is how we have presented it throughout the paper. One calorie is equivalent to 4.18 kJ (the SI unit).
We calculated the actual calorie content of meals by linking the items on the receipt, clarified by the “item questionnaire,” to the calorie content of items listed on restaurant websites. We coded outlier actual or estimated calories as missing if the values exceeded 4000 calories (23 adults, 18 adolescents, and no school age children).
Primary analysis: model 1, overall differences
We used linear regression models to analyze associations with estimated calorie content. In this set of models, we examined estimated calories as the outcome and actual calorie content as the sole predictor. We accounted for clustering by chain (McDonald’s, Burger King, Wendy’s, KFC, Dunkin’ Donuts, and Subway) and by restaurant (identified by the address of each restaurant) with the inclusion of random intercepts for both chain and restaurant. We log transformed estimated and actual meal calorie content because the data were substantially right skewed. We centered the predictor actual calorie content on its mean. Thus, the exponentiated intercepts from these models are the geometric means of the estimated calorie content at the mean actual calorie content. To ensure comparability across models, we included only participants with complete data on all covariates from the second set of models, described below.
Secondary analysis: model 2, factors associated with estimated calorie content
In these models, we added multiple other predictors of estimated calorie content to model 1, including body mass index (BMI), age, sex, race/ethnicity, restaurant chain; how important taste, calories, convenience, or price were in food choices; whether participants noticed calorie information in the restaurant; and accuracy of estimates of daily calorie requirement. We included these covariates because of a priori hypotheses that these variables might be related to calorie estimation. Because we included chain as a predictor in these models, we used random intercepts only for the restaurants; we removed the random intercept for chains. Because we used a log transformation of estimated calories, the exponentiated parameter estimate is the relative change in estimated calorie content per unit increase for linear predictors or compared with a reference group for categorical predictors.
All analyses were conducted with SAS 9.3 (Cary, NC). We performed sensitivity analyses for all outcomes using multiple imputation procedures to account for all missing and outlier data.6 7 Because results were similar, we report only observed findings.
Most participants (1161 (62%) adults, 958 (82%) adolescents, and 262 (81%) school age children) were non-white (table 1⇓). Among the adult participants who provided self reported height and weight, 1173 (65%) were either overweight or obese (BMI ≥25), as were 388 (34%) adolescents and 161 (57%) school age children (BMI ≥85th centile based on 2000 US Centers for Disease Control and Prevention (CDC) age and sex specific reference data). Over 40% of participants in each sample ate at the chain restaurant where they were interviewed at least once a week. When asked whether they noticed calorie information in the restaurant, 410 (22%), 163 (14%), and 51 (15%) responded “yes”, but only 88 (5% of total), 28 (2%), and 14 (4%) reported that they used the information to help guide their purchases.
The mean (SD) actual calorie content of meals purchased was 836 calories (465), 756 calories (455), and 733 calories (359), respectively for adult, adolescent, and school age child participants (equivalent to 3494 (1943), 3160 (1901), 3064 (1501) kJ) (table 2).⇓ At least two thirds of all participants underestimated the calorie content of their meals, with about a quarter underestimating the calorie content by at least 500 calories. The mean difference between estimated and actual meal calorie content showed that participants underestimated calorie content by 175 calories (95% confidence interval 145 to 205 calories), 259 calories (227 to 291 calories), and 175 calories (108 to 242 calories). The mean underestimation of calorie content was larger among Subway diners than those at other chains for adults (349 calories, 293 to 406 calories) and adolescents (500 calories, 429 to 571 calories) with similar values for all chains among school age children (fig 1⇓). With McDonald’s diners as the reference, adult diners at Subway (P<0.001) and Burger King (P=0.01) showed greater underestimation of meal calorie content as did adolescent Subway diners (P<0.001). Adolescent diners at Dunkin’ Donuts had less underestimation of meal calorie content than McDonald’s diners (P=0.008).
Primary and secondary analyses
Primary analysis: model 1, overall differences
When we examined the relation between the logs of actual and estimated calorie content across all chains, accounting for clustering by chain and restaurant, the exponentiated intercepts were 372 calories (95% confidence interval 345 to 402 calories), 268 calories (238 to 298 calories), and 321 calories (265 to 384 calories) for adults, adolescents, and school age children, respectively (table 3⇓). These values are the geometric means of estimated calorie content for participants consuming meals of mean actual calorie content. The geometric means are less than a half of the mean actual calorie content, which shows the underestimation of calorie content.
Secondary analysis: model 2, factors associated with estimated calorie content
In this set of models (table 4⇓ and appendix table), we found a linear association between the logs of actual and estimated calorie content in all samples, with much larger underestimates for larger meals. To show this graphically, we plotted fixed actual calorie contents of meals versus predicted estimated calorie content, calculated from these fully adjusted models for participants with covariates at reference values or means (fig 2⇓).
Adult and adolescent participants dining at Subway estimated 20% and 25% lower meal calorie content than those dining at McDonald’s (relative change 0.80 (95% confidence interval 0.66 to 0.96) for adults and 0.75 (0.57 to 0.99) for adolescents; table 4⇑). In other words, diners at Subway underestimated calorie content by more than diners at McDonald’s. Failure to notice calorie information in the restaurant was not associated with calorie estimates for any of the samples. Underestimation of personal total daily calorie requirements was associated with lower estimated meal calorie content for each sample compared with a “correct” assessment of requirement (0.44 (95% confidence interval 0.38 to 0.52) for adults; 0.50 (0.42 to 0.59) for adolescents; and 0.39 (0.27 to 0.57) for parents of school age children).
Adults with higher BMI estimated higher calorie content of meals (1.12 (95% confidence interval 1.06 to 1.17) per BMI points) and, thus, were less likely to underestimate calorie content (table 4⇑). Among adults, older participants estimated lower calorie content (0.91 (0.88 to 0.95) per 10 years), meaning that for every additional 10 years of age, participants estimated 9% lower calorie content compared with the younger adults. In contrast, older adolescents estimated higher calorie content than younger adolescents, which shows a lower likelihood of underestimation (1.04 (1.02 to 1.08) per year). Black, Hispanic, Asian, and “other” race/ethnicity or multiracial adults and adolescents estimated lower meal calorie content than white participants.
In this study of diners at fast food chain restaurants in four New England cities, we found that participants purchased large meals, and adults, adolescents, and (parents of) school age children underestimated the calorie content of those meals by 175 calories, 259 calories, and 175 calories, respectively. Nearly a quarter of adults, adolescents, and (parents of) school age children underestimated meal calorie content by 500 or more calories. Estimated calorie content was strongly associated with actual calorie content for each of the samples. Noticing calorie information in the restaurant had no effect on the accuracy of calorie estimations.
In a study of 147 fast food restaurant diners at food courts, Chandon and Wansink also found that people underestimated the calorie content of purchased meals, with larger underestimation for higher calorie meals and no association with recognition of nutritional information in the restaurants.2 Compared with that study and other previous research,1 4 our study has the advantages of a large sample size, comparison of diners at six restaurant chains across four cities, recruitment of a racially and ethnically diverse study population in three age groups, and investigation of predictors of underestimation.
Adult and adolescent diners at Subway restaurants estimated lower calorie content than diners at the other chains. These findings suggest a consistent “health halo” for Subway in these age groups. In a study of 518 participants eating meals with equivalent calorie content at McDonald’s and Subway, Chandon and Wansink found that participants estimated 151 fewer calories at Subway than at McDonald’s.3 Participants also ordered side dishes with more calories at Subway. Dieticians also falsely considered equivalent calorie meals to be lower calorie at Subway than McDonald’s.3 Our study extends these findings by showing that this “health halo” is unique to Subway across the six chains and is present across age groups in a diverse sample.
Branding could be an important component of Subway’s “health halo.” Marketing researchers have found that brand positioning is particularly important in guiding consumer choices when specific information about products is not available.8 For example, simply labeling a food item as “heart healthy” led consumers in one experiment to conclude that the item conferred a lower risk of heart disease and stroke than similar unlabeled foods.9 Subway’s positioning as a “healthier” fast food option might lead consumers to view its food as lower calorie, especially when calorie information is not readily apparent.
The forthcoming US federal regulation on labeling calorie content on menus could alter this “health halo” by providing easily accessible information on menus and menu boards.10 11 Previous research has found that information can be most powerful when it contradicts previous expectations (in this case, improper estimation of calorie content of foods with a “health halo”).12 Unlike previous state and local regulations, the federal regulation will also require an anchoring statement that indicates recommended total daily calorie requirements. In our study, participants’ estimates of meal calories strongly correlated with their estimates of total daily requirements, supporting inclusion of daily requirements on menus as an “anchor.” Thus far, research about the effects of calorie menu labeling, in both real world and experimental settings, has been mixed.1 13 14 15 16 17 18 19 20 21 22 23 24 25 26 It is difficult to ascertain why these studies had inconsistent results, but differing study designs, demographic characteristics, the rare use of an anchoring statement, and weight status might be involved.
In addition to providing an anchoring statement on menus, policymakers could perhaps improve menu labeling by supporting social marketing campaigns to better explain the concept of calories. These efforts could bolster not only menu labeling but nutritional labeling of packaged foods.
Limitations of study
There are several limitations to our study. First, because more than half of eligible individuals did not participate, the participants in our study might not represent all customers of the restaurants. It is somewhat reassuring that the sex ratio of respondents and non-respondents was similar, but sex was the only information that we were able to collect on non-respondents. While our response rate seems low, this rate was higher than we anticipated for the fast paced environments where we collected data. The low response could bias the results in either direction. Participants who did not have time to respond to our survey might also have been less aware of nutritional information in restaurants than those who did respond. Thus, our respondents might represent a group less likely to underestimate, biasing our results toward the null. In contrast, some potential participants with higher education, perhaps better able to estimate calorie content, might have ignored our monetary incentive. As a result, our respondents might have been less aware of calorie content than the overall population, biasing our results away from the null. Telephone or household surveys could have yielded higher response rates but would not allow collection of receipts needed to objectively determine the calorie content of meals. Second, we could not sample customers in the drive through section of restaurants, whose behavior might differ from that of walk in customers. Third, we could not measure actual calorie consumption by weighing food before and after consumption, as would be possible in a laboratory setting. Instead, we collected receipts and asked detailed questions about items participants purchased for their personal consumption. Fourth, because we developed the questionnaire to be brief, we collected only basic demographic information, height, and weight on participants. We were unable to collect additional health information that could affect estimation of calorie content.
In this study of over 3000 diners at six fast food restaurant chains across four diverse New England cities, we found that adults, adolescents, and parents of school age children generally underestimated the calories of meals, especially if the meal was large. Adults and adolescents dining at Subway underestimated calorie content more than diners at other chains. The forthcoming calorie menu labeling requirements of the US Patient Protection and Affordable Care Act might help to correct underestimation of calorie content.
What is already known on this topic
Consumers are known to underestimate the calorie content of restaurant meals, especially for large calorie meals
Previous studies have been conducted in experimental settings without monitoring consumer choices at actual fast food restaurants, have focused on a narrow range of fast food restaurants, or have enrolled samples with limited racial/ethnic or age group diversity
What this study adds
All age groups and racial/ethnic groups studied underestimated the calorie content of meals from fast food restaurants
Cite this as: BMJ 2013;346:f2907
We thank Angela Bannister, Anthony Bean, Deborah Burton, Alanna Burwell, Hilda Castillo, Jamie Chachere, Alicia Johnson, Elise Lauer, Rose Nabehet, Christine Orcutt, Diedra Oretade, Liberty Pande, Maricelle Ramirez, Elyse Rohrer, and Jordan Warner for their help with data collection.
JPB presented some results from this study at the Annual Meeting of the Society of General Internal Medicine in May 2011, the Annual Meeting of The Obesity Society in October 2011, and the Annual Meeting of The Obesity Society in September 2012.
Contributors: JPB, SKC, KK, JM, SL, and MWG conceptualized the study design and the data collection strategy. JPB, KK, and SR-S conducted the data analyses, and MWG provided critical feedback on the analyses. JPB drafted the manuscript, and SKC, KK, JM, SL, SR-S, and MWG revised the manuscript. All authors approved the final version of the manuscript. JPB is guarantor.
Funding: The study was funded by a P30 center grant from the National Heart, Lung, and Blood Institute (P30 HL101312-01, PI: Gillman), a Robert Wood Johnson Foundation Health and Society Scholars seed grant from the Harvard University site (PI: Block), the Robert Wood Johnson Foundation Healthy Eating Research program (grant 70739, PI: Block), and the Robert H Ebert Fellowship, funded by the Harvard Pilgrim Health Care Foundation through the Eleanor and Miles Shore Fellowship Program at Harvard Medical School (PI: Block). The sponsors of this study had no role in the study design, data collection, or analysis for this study and did not require final approval of the manuscript.
Competing interests: All authors have completed the ICMJE uniform disclosure form at www.icmje.org/coi_disclosure.pdf (available on request from the corresponding author) and declare: JPB, KK, SL, SR-S received salary support from the National Heart, Lung, and Blood Institute (NIH) for the submitted work; JPB, SL, and SR-S received support from the Robert Wood Johnson Health Eating Research program; and JPB and SL received support from the Ebert Fellowship.
Ethical approval: The study was approved by the institutional review board of Harvard Pilgrim Health Care (approval 0311). Because data collection was anonymous and queried non-sensitive information, the board approved this study without requiring written informed consent from participants. For the same reasons, the board also granted permission for us to interview those aged 11-20, included in the adolescent sample, without parental consent.
Data sharing: No additional data available.
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