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Evidence Summary: Collaborative Modeling of U.S. Breast Cancer Screening Strategies

Other Supporting Document for Breast Cancer: Screening

Collaborative Modeling of the Benefits and Harms Associated With Different U.S. Breast Cancer Screening Strategies

By Jeanne S. Mandelblatt, MD, MPH; Natasha K. Stout, PhD; Clyde B. Schechter, MA, MD; Jeroen J. van den Broek, MS; Diana L. Miglioretti, PhD; Martin Krapcho, BS; Amy Trentham-Dietz, PhD, MS; Diego Munoz, PhD, MS; Sandra J. Lee, ScD; Donald A. Berry, PhD; Nicolien T. van Ravesteyn, PhD; Oguzhan Alagoz, PhD; Karla Kerlikowske, MD; Anna N.A. Tosteson, ScD; Aimee M. Near, MPH; Amanda Hoeffken, MPH; Yaojen Chang, DrPH, MS, MPH; Eveline A. Heijnsdijk, PhD; Gary Chisholm, MS; Xuelin Huang, PhD; Hui Huang, MS; Mehmet Ali Ergun, MSc; Ronald Gangnon, PhD; Brian L. Sprague, PhD; Sylvia Plevritis, PhD; Eric Feuer, PhD; Harry J. de Koning, MD, PhD; and Kathleen A. Cronin, PhD, MPH


The information in this article is intended to help clinicians, employers, policymakers, and others make informed decisions about the provision of health care services. This article is intended as a reference and not as a substitute for clinical judgment.

This article may be used, in whole or in part, as the basis for the development of clinical practice guidelines and other quality enhancement tools, or as a basis for reimbursement and coverage policies. AHRQ or U.S. Department of Health and Human Services endorsement of such derivative products may not be stated or implied.

This article was published online first at www.annals.org on January 12, 2016.

Abstract

Background: Controversy persists about optimal mammography screening strategies.

Purpose: To evaluate screening outcomes, taking into account advances in mammography and treatment of breast cancer.

Design: Collaboration of 6 simulation models using national data on incidence, digital mammography performance, treatment effects, and other-cause mortality.

Setting: United States.

Patients: Average-risk US female population and subgroups with varying risk, breast density, or comorbidity.

Intervention: Eight strategies differing by age at which screening starts (40, 45, or 50 years) and screening interval (annual, biennial, and hybrid [annual for women in their 40s and biennial thereafter]). All strategies assumed 100% adherence and stopped at age 74 years.

Measurements: Benefits (breast cancer–specific mortality reduction, breast cancer deaths averted, life-years, and quality-adjusted life-years); number of mammograms used; harms (false-positive results, benign biopsies, and overdiagnosis); and ratios of harms (or use) and benefits (efficiency) per 1000 screens.

Results: Biennial strategies were consistently the most efficient for average-risk women. Biennial screening from age 50 to 74 years avoided a median of 7 breast cancer deaths versus no screening; annual screening from age 40 to 74 years avoided an additional 3 deaths, but yielded 1988 more false-positive results and 11 more overdiagnoses per 1000 women screened. Annual screening from age 50 to 74 years was inefficient (similar benefits, but more harms than other strategies). For groups with a 2-to 4-fold increased risk, annual screening from age 40 years had similar harms and benefits as screening average-risk women biennially from 50 to 74 years. For groups with moderate or severe comorbidity, screening could stop at age 66 to 68 years.

Limitation: Other imaging technologies, polygenic risk, and nonadherence were not considered.

Conclusion: Biennial screening for breast cancer is efficient for average-risk populations. Decisions about starting ages and intervals will depend on population characteristics and the decision makers' weight given to the harms and benefits of screening.

Primary Funding Source: National Institutes of Health.

Introduction

Despite decades of mammography screening for early detection of breast cancer, there is no consensus on optimal strategies, target populations, or the magnitude of harms and benefits.1–11 The 2009 U.S. Preventive Services Task Force (USPSTF) recommended biennial film mammography from age 50 to 74 years and suggested shared decision making about screening for women in their 40s.12 Since that recommendation was formulated, new data on the benefits of screening have emerged,2, 6, 8, 9, 11, 13, 14 digital mammography has essentially replaced plain film,15 and increasingly effective systemic treatment regimens for breast cancer have become standard.16 There has also been growing interest in consumer preferences and personalized screening approaches.17–20 These factors could each affect the outcomes of breast cancer screening programs or alter policy decisions about population screening strategies.17

Modeling can inform screening policy decisions because it uses the best available evidence to evaluate a wide range of strategies while holding selected conditions (such as treatment effects) constant, facilitating strategy comparisons.21, 22 Modeling also provides a quantitative summary of outcomes in different groups and assesses how preferences affect results. Collaboration of several models provides a range of plausible effects and illustrates the effects of differences in model assumptions on results.1, 7, 23

We used 6 well-established simulation models to synthesize current data and examine the outcomes of digital mammography screening at various starting ages and intervals among average-risk women. We also examined how breast density, risk, or comorbidity levels affect results and whether preferences for health states related to screening and its downstream consequences affected conclusions.

Methods

Strategies

We evaluated 8 strategies that varied by starting age (40, 45, or 50 years) and interval (annual, biennial, and hybrid [annual for women in their 40s and biennial thereafter]); all strategies stop screening at age 74 years. We included "no screening" as a baseline.

Model Descriptions

The models used to evaluate the screening strategies were developed within the Cancer Intervention and Surveillance Modeling Network (CISNET),24–30 and the research was institutional review board–approved. They were named model D (Dana-Farber Cancer Institute, Boston, Massachusetts), model E (Erasmus MC, University Medical Center Rotterdam, Rotterdam, the Netherlands), model GE (Georgetown University Medical Center, Washington, DC, and Albert Einstein College of Medicine, Bronx, New York), model M (MD Anderson Cancer Center, Houston, Texas), model S (Stanford University, Stanford, California), and model W (University of Wisconsin, Madison, Wisconsin, and Harvard Medical School, Boston, Massachusetts). The Appendix provides information on model validation.

Since earlier analyses,1 the models have undergone substantial revision to reflect advances in breast cancer control, including portrayal of molecular subtypes based on estrogen receptor (ER) and human epidermal growth factor-2 receptor (HER2) status;23 current population incidence31and competing non–breast cancer mortality; digital screening; and the most current therapies.32 All models except model S include ductal carcinoma in situ (DCIS).

The general modeling approach is summarized in this article; full details, including approach, construction, data sources, assumptions, and implementation, are available at https://resources.cisnet.cancer.gov/registry and reference 33. Additional information is available on request, and the models are available for use via collaboration.

The models begin with estimates of breast cancer incidence31 and ER/HER2-specific survival trends without screening or adjuvant treatment, and then overlay data on screening and molecular subtype–specific adjuvant treatment to generate observed incidence and breast cancer–specific mortality trends in the U.S. population.1, 7, 17, 23, 33, 34 Breast cancer has a distribution of preclinical screen-detectable periods (sojourn time) and clinical detection points. Performance characteristics of digital mammography depend on age, first versus subsequent screen, time since last mammogram, and breast density. ER/HER2 status is assigned at diagnosis on the basis of stage and age. Molecular subtype– and stage-specific treatment reduces the hazard of breast cancer death (models D, GE, M, and S) or results in a cure for some cases (models E and W). Women can die of breast cancer or other causes. Screen detection of cancer during the preclinical screen-detectable period can result in the identification and treatment of earlier-stage or smaller tumors than might occur via clinical detection, with a corresponding reduction in breast cancer mortality.

We used a cohort of women born in 1970 with average-risk and average breast density and followed them from age 25 years (because breast cancer is rare before this age [0.08% of cases]) until death or age 100 years.

Model Input Parameters

The models used a common set of age-specific variables for breast cancer incidence, performance of digital mammography, treatment effects, and average and comorbidity-specific non–breast cancer causes of death.20, 34, 35 The parameter values are available at www.uspreventiveservicestaskforce.org/Page/Document/modeling-report-collaborative-modeling-of-us-breast-cancer-1/breast-cancer-screening1.34 In addition, each group included model-specific inputs (or intermediate outputs) to represent preclinical detectable times, lead time, and age- and ER/HER2- specific stage distribution in screen- versus non–screen-detected women on the basis of their specific model structure.1, 7, 23–30 These model-specific parameters were based on assumptions about combinations of values that reproduced U.S. trends in incidence and breast cancer–specific mortality, including proportions of DCIS that were nonprogressive and would not be detected without screening. Models M and W also assumed some small nonprogressive invasive cancers.

The models adopted an age–period–cohort modeling approach to project incidence rates of breast cancer in the absence of screening;31, 36 model M used 1975–1979 rates from the Surveillance, Epidemiology, and End Results program. The models assumed 100% adherence to screening and receipt of the most effective treatment to isolate the effect of varying screening strategies.

Four models used age-specific sensitivity values for digital mammography that were observed in the Breast Cancer Surveillance Consortium (BCSC) for detection of invasive and DCIS cancers combined (model S uses data for invasive cancers only). Separate values were used for initial and subsequent mammography by screening interval, using standard BCSC definitions: "Annual" includes data from screens occurring within 9 to 18 months of the prior screen, and "biennial" includes data on screens within 19 to 30 months.37, 38 Model D used these data as input variables,28 and models GE, S, and W used the data for calibration.24, 25, 27 Models E and M fit estimates from the BCSC and other data.26, 29

Women with ER-positive tumors received 5 years of hormone therapy and an anthracycline-based regimen accompanied by a taxane. Women with ER-negative invasive tumors received anthracycline-based regimens with a taxane. Those with HER2-positive tumors also received trastuzumab. Women with ER-positive DCIS received hormonal therapy.16 Treatment effectiveness was based on clinical trials and was modeled as a reduction in breast cancer–specific mortality risk or increase in the proportion cured compared with ER/HER2-specific survival in the absence of adjuvant treatment.32

Benefits

Screening benefits (vs. no screening or incremental to other strategies) included percentage of reduction in breast cancer mortality, breast cancer deaths averted, and life-years and quality-adjusted life-years (QALYs) gained because of averted or delayed breast cancer death. Benefits (and harms) were accumulated from age 40 to 100 years to capture the lifetime effect of screening.

We considered preferences, or utilities, to account for morbidity from screening and treatment. A disutility for age- and sex-specific general population health was first applied to quality-adjust the life-years.39 These were further adjusted to account for additional decrements in life-years related to undergoing screening (–0.006 for 1 week, or –1 hour), evaluating a positive screen (–0.105 for 5 weeks, or –3.7 days), undergoing initial treatment by stage (for the first 2 years after diagnosis), and having distant disease (for the last year of life for all women who die of breast cancer) (Appendix Table 1).33, 40, 41

Use and Harms

Use of services focused on the number of mammograms required for the screening strategy. Harms included false-positive mammograms, benign biopsies, and overdiagnosis. Rates of false-positive mammograms were calculated as mammograms read as abnormal or needing further work-up in women without cancer divided by the total number of screening mammograms. Benign biopsies were defined as biopsies among women with false-positive screening results; we assumed 100% compliance with biopsy recommendations.42 Overdiagnosis was defined as all cases that would not have been clinically detected in the absence of screening because of lack of progressive potential or death from competing non–breast cancer mortality. The effect of overdiagnosis on QALYs was captured by the disutility of being treated for cancer but dying of other causes.

Statistical Analysis

For each model, strategies were ranked by the number of mammograms performed. We report the median use, benefits, and harms and range across models. We also obtained an efficiency frontier by plotting the sequence of points that represent the largest incremental percentage of reduction in breast cancer mortality (or life-years or QALYs) per mammogram performed or harm entailed. Screening strategies that fell on this frontier were considered the most efficient (that is, they have the steepest slope such that no alternative exists that provides more benefit with less use or fewer harms).

Three models (E, GE, and W) also evaluated results based on combinations of breast cancer risk and density. Risk levels included 1.3 times higher than average (for example, nulliparity or age at first live birth >30 years);18, 43 2.0 times higher than average (for example, family history of 1 first-degree relative);18 or 4.0 times higher than average (for example, family history of 2 or more first-degree relatives).18, 44 Greater risk levels, such as those seen with BRCA1 and BRCA2 mutations, were not considered because such groups have specific screening guidelines. We made the simplifying assumption that risk affected incidence, but not other aspects of disease.

Breast density was modeled as entirely fatty ("a"), scattered density ("b"), heterogeneously dense ("c") and extremely dense ("d"). On the basis of observed age-specific prevalence rates, density was assigned at age 40 years and remained the same or decreased by 1 level at age 50 years and again at age 65 years.45 Density modified the sensitivity and specificity of mammography on the basis of age, interval, and first versus subsequent screening.33 Density also modified the age group–specific (40 to 49 years, 50 to 64, and ≥65 years) risk for breast cancer, using age-group-specific risk among those with average population density as the referent category (BCSC. Unpublished data).44, 46 Density was assumed not to affect molecular subtype or disease natural history. Results for density were grouped into low ("a and b") or high ("c and d") for presentation. The risk- and density-specific results were also compared with those for screening average-risk and average-density groups biennially from 50 to 74 years, because many guideline groups accept the latter.

In other analyses, 2 models (model E and GE) examined the effect of comorbidity on screening cessation by using comorbidity-specific life expectancy groups. Examples of conditions that placed women in severe and moderate comorbidity groups included congestive heart failure and diabetes, respectively; the specific conditions and their associated life expectancies are reported elsewhere.20, 35, 47 We compared results of continuing to screen biennially past age 74 years among women with no or low comorbidity or stopping earlier than 74 years for those with moderate or high comorbidity. These analyses included women who survived and were free of breast cancer up until the point where screening was to be extended or stopped.

Four models evaluated whether high disutility values would eliminate screening benefits. Finally, we evaluated the ability of the models to independently predict external trends and results (Appendix Figure 1 and Appendix Table 2).

Role of the Funding Source

We worked with the USPSTF and Agency for Healthcare Research and Quality (AHRQ) to develop the scope and key questions for this research. National Cancer Institute investigators (K.C., E.F.) collaborated in their role as scientific project officers. AHRQ staff distributed earlier versions of the draft for peer review. The agencies had no role in the study conduct or decision to submit the manuscript for publication. The investigators are solely responsible for the content and the decision to submit the manuscript for publication.

Results

Benefits in the Average-Risk Population

The models produced consistent rankings of the screening strategies (Table 1). For instance, biennial screening from age 50 to 74 years yielded a median 25.8% reduction in breast cancer mortality compared with no screening (range, 24.1% to 31.8%). Annual screening led to slightly greater reductions in mortality than biennial strategies. However, biennial strategies maintained a median of 79.8% to 81.3% of the breast cancer–specific mortality reduction of annual screening (range, 68.3% to 98.9%) (Appendix Table 3).

Biennial screening also maintained the most annual benefits for life-years and QALYs, and quality adjustment did not change the ranking of strategies. Across all strategies, the largest decrement from quality adjustment to life-years was related to declines in general health as women aged; smaller decrements occurred owing to the disutility of undergoing diagnostic evaluation of an abnormal screening examination and for having cancer. The disutility associated with screening itself had a minimal effect on QALYs.33

The incremental benefits of initiating screening at age 40 years were slightly greater than those of starting at age 50 years in terms of breast cancer deaths averted with both annual and biennial screening (median, 1.3 [range, 1.1 to 1.7] and 1.0 [0.8 to 1.7] per 1000 women screened, respectively) (Table 2). Initiating screening at age 45 years yielded benefits intermediate between beginning at 40 and 50 years, although there were slightly greater incremental benefits when starting at age 45 years (vs. 50 years) than starting at age 40 years (vs. 45 years) (for example, 10.6 vs. 8.0 and 15.4 vs. 7.9 QALYs for biennial and annual strategies, respectively) (Table 1).

Harms in the Average-Risk Population

All models projected more harms (false-positive results, benign biopsies, and overdiagnosed cases) under annual versus biennial schedules and by starting earlier than age 50 years versus at age 50 years (Table 3). For instance, if biennial screening began at age 40 years instead of age 50 years, for every 1000 women screened there would be a median of 1 more death averted, but 576 more false-positive results, 67 more benign biopsies, and 2 additional overdiagnosed cases. Compared with screening initiation at age 45 years, starting screening at age 40 years had 1 or fewer added deaths averted depending on interval, but more incremental harms.

Efficiency Frontiers for Average-Risk Populations

Efficiency frontier plots were used to graphically depict the balance between the number of mammograms and benefits (life-years gained) of screening strategies. Biennial strategies starting at age 40, 45, or 50 years were all efficient (Figure 1 and Appendix Figure 2). Points that were close to but fell below the frontier were less efficient than those on the frontier line. For example, compared with the point on the efficient frontier for biennial screening at age 45 years, the hybrid strategy of annual screening at 45 years was less efficient than biennial screening starting at 40 years. This is because the hybrid strategy at 45 years would require 405.8 more mammograms to gain an additional life-year for every 1000 women screened compared with biennial screening at 45 years, whereas biennial screening starting at 40 years would require only 189.5 extra mammograms to gain an additional life-year.

Finally, annual screening from age 50 to 74 years was consistently inferior to other strategies (that is, it was inefficient, or dominated) because it yielded the same or fewer benefits than the next less resource intensive efficient strategy but required more mammograms or entailed more harms (for example, A50 vs. B40 in Figure 1). These patterns were generally seen with other harm and benefit metrics (Appendix Figure 2).

Sensitivity Analyses for Average-Risk Populations

Varying the disutilities for usual health, screening, diagnosis, and treatment did not affect strategy rankings for average-risk populations, and QALY gains persisted under all screening strategies, although their magnitude decreased with increasing disutility.33

Harms and Benefits, by Risk Level

The balance of harms and benefits differed by risk group, with women at higher risk having fewer false-positive results per 1000 women screened and higher gains from screening than lower-risk groups. Screening higher-risk women also yielded a lower ratio of overdiagnosed cases per breast cancer death averted than screening average-risk women. However, annual screening from age 50 to 74 years had the same or less benefit and more harms than other strategies at all risk levels.33

For women with a 2- to 4-fold increase in risk, annual screening starting at age 40 or 45 years had similar or more favorable harm–benefit ratios (on the basis of false-positive results) as biennial screening of average-risk women from 50 to 74 years of age. If the harm–benefit ratio of 185.8 (range, 169.5 to 268.0) false-positive results per death averted for average-risk women screened biennially from 50 to 74 years of age is considered to be acceptable, then for women with a 2- to 4-fold increase in risk, annual screening starting at age 40 or 45 years had similar or more favorable harm–benefit ratios. For instance, women with a 2-fold increase in risk undergoing annual screening at age 40 years have a slightly more favorable corresponding ratio, at 182.5 (range, 177.4 to 231.9) false-positive results per death averted. For women with a 1.3-fold increase in risk, biennial screening starting at age 40 years had similar harm–benefit ratios as biennial screening of average-risk women from age 50 to 74 years.

Benefits and Harms, by Breast Density Group

Breast density (low vs. high) changed absolute benefits, but annual screening from 50 to 74 years remained inefficient across breast density groups. Women in the low-density group had a greater proportion of their cancers detected owing to greater sensitivity of digital mammography, and therefore a greater reduction in breast cancer–specific mortality than the high-density group. However, women in the high-density group had a greater absolute number of cancer cases detected because their risk for cancer was higher, leading to more life-years saved among these women than in the low-density group.33

Benefits and Harms, by Comorbidity

For women with no comorbidity, biennial screening could continue to age 78 or 80 years and still have similar harm–benefit ratios as screening women with average non–breast cancer mortality biennially from 50 to 74 years. However, for women with moderate to severe comorbidity, the comparable ratios were equivalent at about age 66 to 68 years.33

Discussion

We used 6 established models to estimate the potential efficacy of different strategies in the United States. All 6 models demonstrated that screening initiation at age 40 years has some benefits for average-risk populations, but also higher levels of harms, than strategies starting at age 50 years. The findings also suggest that comorbidity levels could be used to tailor the age of screening cessation. Biennial screening strategies were the most efficient, but annual screening could be considered from age 40 to 74 years in groups with a 2- to 4-fold higher-than- average risk.

Results from all models indicated that digital mammography screening of average-risk women in their 40s modestly lowers breast cancer–specific mortality and extends the length and quality of life, even after disutilities related to the screening process are considered. The absolute benefits of starting screening in the 40s varied somewhat on the basis of model structure and assumptions, but were consistent with observations from randomized trials.6 However, starting at age 40 versus 45 years was associated with increasing incremental harms relative to the increase in benefits. Thus, decisions about initiating screening before age 50 years may depend on the weight attached to screening benefits and harms.

Consistent with other analyses of upper age limits for screening20, 48–50and other recommendations,12, 51 our results suggested that the balance of harms and benefits of screening was affected by competing non–breast cancer mortality, so that age at screening cessation could be tailored by comorbidity levels.

Similar to our 2009 analysis,1 biennial strategies are most consistently efficient. Screening annually from age 50 to 74 years had the same or fewer benefits for any given harm for all population groups in virtually all models and would be considered inefficient. However, annual screening in the 40s followed by biennial screening at age 50 years, and the most intensive schedule evaluated (annual screening from 40 to 74 years), were also efficient or close to being efficient. In addition, annual screening of women with a 2- to 4-fold increased risk (for example, due to non–BRCA-related family history) from age 40 to 74 years had harm–benefit ratios similar to those of biennial screening from age 50 to 74 years in average-risk populations.

The results also suggest that benefits of screening vary by breast density, at least when grouped into low and high categories. Women with dense breasts have a higher risk for cancer and a higher absolute detection rate, but a lower relative detection rate.19, 52 This is because the sensitivity of digital mammography, although optimized for density, is still lower in women with dense breasts than those with nondense breasts.53–56 Improving outcomes for women with dense breasts55 may require new innovations in imaging57–60 or identification of risk biomarkers.61, 62

This analysis extends our prior work by explicitly considering overdiagnosis as a screening harm. Depending on screening strategy, the models estimated that 2% to 12% of invasive disease cases and 30% to 50% of DCIS cases might represent overdiagnosis. Although the models differed in absolute estimates, they agreed on how overdiagnosis affected the ranking of strategies and the finding that most overdiagnosed cases were DCIS. The model results for overdiagnosis are not directly comparable with other published estimates8, 63 because the models followed women for their entire lives. The models also made assumptions about unobservable input parameters related to natural history. Although there is no agreement on methods to estimate overdiagnosis64 or on its true rate,65, 66 there is agreement that it is an important harm. Active surveillance for DCIS with a low risk for progression is one potential future approach to reduce harms from DCIS overdiagnosis. More information is also needed on consumer knowledge of and willingness to risk overdiagnosis.67

Overall, this study has several important strengths, including collaboration of 6 long-established, independent modeling groups; use of well-calibrated models that reproduce temporal epidemiologic trends and a screening trial result; inclusion of digital technology; incorporation of increasingly effective treatments; and consideration of quality of life, risk factors, breast density, and comorbidity.68 The conclusions about the ranking of screening strategies are robust and should provide greater credibility than inferences based on 1 model alone.

Our study also had limitations. First, to evaluate program efficacy, we assumed 100% adherence to screening, prompt evaluation of abnormal results, and full use of optimal treatment. Actual benefits will fall short of our projected results because adherence is not perfect.

Second, we focused only on hybrid strategies for women in their 40s. Alternative hybrid strategies may be important to examine in future research.

Third, the analysis did not consider other imaging technologies for average-risk populations or for groups with high breast density; such technologies include ultrasonography,69 computer-aided detection,70 tomosynthesis, or magnetic resonance imaging. Data on tomosynthesis performance and needs for radiologist retraining are still emerging.58

Fourth, we did not model any radiation-induced breast cancers, owing to more intensive mammography schedules.71 Fifth, we assumed that risk factors influenced the incidence of disease, but not its natural history.

Sixth, certain risk factors, such as family history, are age-dependent in their effects.18, 72 Because we held relative risk levels constant over age, our benefit estimates could be over- or underestimated for specific risk factors.17

Seventh, we did not consider polygenic risk73, 74 or explicitly model menopausal status; we used age 50 years as a proxy for the average age of menopause. Eighth, the analysis did not include screening program costs or utility estimates specific to some of the newest treatments.

Finally, compared with our earlier research,1 the models all estimated similar, but somewhat greater, reductions in breast cancer–specific mortality (for example, a median 22% vs. 25.8% reduction with biennial screening from 50 to 74 years in 2009 vs. current models, respectively). The primary reasons for this modeled improvement relate to the increased sensitivity of digital compared with film mammography, advances in molecular-targeted therapies, and changes in underlying breast cancer trends.

Overall, the 6 models conclude that biennial screening strategies are the most efficient. Choices about the optimal age at initiation (and cessation) and screening intervals will ultimately depend on program goals, the weight attached by the decision maker to screening harms and benefits,75 and considerations of efficiency.

Copyright and Source Information

Source: This article was published at www.annals.org on January 12, 2016.

Note: Portions of earlier versions of this research were presented on the USPSTF Web site as part of a Technical Report (AHRQ publication no. 14-05201-EF-4).33

Note: This work was done by 6 independent modeling teams, for the Breast Cancer Working Group of the Cancer Intervention and Surveillance Modeling Network (CISNET) and the Breast Cancer Surveillance Consortium (BCSC). The teams were from Dana-Farber Cancer Institute (principal investigator [PI], Dr. Lee); Erasmus MC, University Medical Center Rotterdam (PI, Dr. de Koning); Georgetown University Medical Center, Lombardi Comprehensive Cancer Center (PI, Dr. Mandelblatt) and Albert Einstein College of Medicine (PI, Dr. Schechter); Harvard Medical School and Harvard Pilgrim Health Care (PI, Dr. Stout) and University of Wisconsin (PIs, Drs. Trentham-Dietz and Alagoz); University of Texas MD Anderson Cancer Center (PI, Dr. Berry); and Stanford University (PI, Dr. Plevritis). Drs. Mandelblatt, Cronin, de Koning, Miglioretti, Schechter, and Stout were the coordinating committee for the project; Drs. Mandelblatt, Stout, Schechter, and Cronin were the writing committee; Drs. de Koning and Cronin served as dual senior authors; and Dr. Feuer was responsible for overall CISNET project direction. The BCSC collaborated and also provided key data inputs to the modeling teams. Members of the BCSC are listed at http://breastscreening.cancer.gov.

Disclaimer: The investigators worked with members of the USPSTF and AHRQ staff to develop the scope and key questions for this research. The USPSTF, AHRQ, and the funding sources had no role in study conduct. AHRQ staff distributed earlier versions of the draft for peer review. The investigators are solely responsible for the content and the decision to submit the manuscript for publication.

Acknowledgment: The authors thank CISNET consultants Elizabeth Burnside, Allison Kurian, Donald Weaver, and Diana Buist for review of earlier versions of the models for structure, parameters, and assumptions for clinical face validity; Jennifer Croswell from AHRQ for assistance with analysis and review of results; members of the USPSTF and the Oregon Evidence-based Practice Center for comments on earlier versions of this research; and Jessica Garshell for data processing. They also thank Adrienne Ryans for manuscript preparation and John Wong, Stuart Baker, William Lawrence, and Tom Trikalinos for helpful suggestions on earlier versions of this paper.

Grant Support: By the National Institutes of Health (National Cancer Institute grant U01 CA152958 and National Cancer Institute–funded BCSC grant P01 CA154292, contract HSN261201100031C, and grant U54CA163303), and in part by American Cancer Society grant MRSG 14-027-01 CPHPS (Dr. Chang). The collection of BCSC cancer and vital status data used in this study was supported in part by several state public health departments and cancer registries throughout the United States. A full list of BCSC investigators and a description of these sources is available at http://breastscreening.cancer.gov/work/acknowledgement.html.

Disclosures: Dr. Stout reports grants from the National Cancer Institute during the conduct of the study. Dr. Schechter reports grants from the National Cancer Institute during the conduct of the study. Dr. Miglioretti reports grants from AHRQ and the National Cancer Institute during the conduct of the study. Dr. Trentham-Dietz reports grants from the National Cancer Institute during the conduct of the study. Dr. van Ravesteyn reports grants from the National Cancer Institute during the conduct of the study. Dr. Alagoz reports grants from the National Cancer Institute during the conduct of the study. Dr. Tosteson reports grants from the National Cancer Institute during the conduct of the study. Dr. Heijnsdijk reports grants from SCOR and personal fees from the American Society of Breast Surgeons outside the submitted work. Dr. Gangnon reports grants from the National Cancer Institute during the conduct of the study. Dr. Sprague reports grants from the National Institutes of Health during the conduct of the study. Dr. de Koning reports grants from the National Cancer Institute during the conduct of the study. Authors not named here have disclosed no conflicts of interest. Disclosures can be viewed at www.acponline.org/authors/icmje/ConflictOfInterestForms.do?msNum=M15-1536.

Requests for Single Reprints: Jeanne S. Mandelblatt, MD, MPH, Lombardi Comprehensive Cancer Center, 3300 Whitehaven Street, NW, Suite 4100, Washington, DC 20007; e-mail, mandelbj@georgetown.edu.

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Appendix: Model Validation

Each model has a different structure and assumptions and some varying input variables, so no single method can be used to validate results against an external standard. Therefore, we used several approaches.

First, considering actual screening and treatment patterns instead of the efficacy strategies simulated in the base case, we compared model projections of incidence, breast cancer–specific mortality, and stage distribution with those reported by the Surveillance, Epidemiology, and End Results program for 1975 to 2010. In our previous work, results of each model accurately projected trends for incidence and breast cancer–specific mortality by ER status for 1975 to 2000.23 Next, we approximated the Age screening trial,6 assuming perfect adherence to invitations for annual screening with 13-year follow-up of women aged 40 to 49 years.6 Finally, we examined the consistency of results across models.

Using inputs for actual dissemination of screening and treatment in the United States, the models captured the major trends in incidence and the general shape of breast cancer–specific mortality decreases over time (Appendix Figure 1). They also closely matched current stage distribution (not shown) and the Age trial results (Appendix Table 2).6, 33

Thus, the models replicated patterns of observed US incidence and breast cancer–specific mortality over time. The models also estimated similar breast cancer–specific mortality reduction as that observed among women aged 40 to 49 years who actually attended screening in the Age trial, although the model results are slightly more optimistic than the trial because the models assume 100% screening and use of the most effective systemic regimens.6 Overall, use of 6 models to project a range of plausible screening outcomes provides implicit cross-validation, with the range of results from the models as a measure of uncertainty.

Table 1. Ranking of Benefits per 1000 Women Screened, by Model and Screening Strategy

Strategy* Screens, n Model Median
(Range Across
Models), %
D E GE M S W
Reduction in Breast Cancer Mortality per 1000 Women Screened vs. No Screening, %
Biennial, 50−74 11,127 25.6 26.0 31.8 26.8 24.1 25.4 25.8 (24.1−31.8)
Biennial, 45−74 13,212 26.6 27.6 33.9 28.4 25.9 26.7 27.2 (25.9−33.9)
Hybrid, 45−74 15,966 27.7 29.7 35.9 29.2 27.3 30.1 29.5 (27.3−35.9)
Biennial, 40−74 16,013 28.3 30.3 35.9 31.9 28.2 30.5 30.4 (28.2−35.9)
Hybrid, 40−74 20,884 29.0 32.3 37.9 31.7§ 29.3 32.8 32.0 (29.0−37.9)
Annual, 50−74 21,318 32.1 33.9 37.6§ 27.1§ 29.1§ 35.3 33.0 (27.1−37.6)
Annual, 45−74 26,136 34.2 37.6 41.6 29.4§ 32.3 39.1 35.9 (29.4−41.6)
Annual, 40−74 31,037 35.5 40.1 43.6 32.5 34.4 42.6 37.8 (32.5−43.6)
Years of Life Gained per 1000 Women Screened vs. No Screening*
Biennial, 50−74 11,127 153.8 94.0 140.5 146.5 104.2 74.6 122.4 (74.6−153.8)
Biennial, 45−74 13,212 168.4 107.7 161.2 171.3 115.2 84.0 138.2 (84.0−171.3)
Hybrid, 45−74 15,966 175.3 117.9 170.2 171.4 125.1 95.7 147.7 (95.7−175.3)
Biennial, 40−74 16,013 183.7 123.7 172.4 194.8 131.6 98.8 152.0 (98.8−194.8)
Hybrid, 40−74 20,884 191.1 137.6 187.2 211.5 141.0 110.9 164.1 (110.9−211.5)
Annual, 50−74 21,318§ 180.0§ 125.9§ 167.3§ 156.3§ 133.3§ 104.3§ 144.8 (104.3−180.0)§
Annual, 45−74 26,136 201.3 149.3 196.7 177.8§ 154.2 123.0 166.0 (123.0−201.3)
Annual, 40−74 31,037 217.1 168.8 213.5 218.1 170.1 140.5 191.8 (140.5−218.1)
QALYs Gained per 1000 Women Screened vs. No Screeningǁ
Biennial, 50−74 11,127 114.5 67.3 100.1 109.6 71.9 47.1 86.0 (47.1−114.5)
Biennial, 45−74 13,212 123.8 75.6 114.4 129.4 78.8 51.9 96.6 (51.9−129.4)
Hybrid, 45−74 15,966 126.6 80.9 118.3 128.5 84.5 58.3 101.4 (58.3−128.5)
Biennial, 40−74 16,013 133.7 85.4 120.1 148.1 89.1 60.4 104.6 (60.4−148.1)
Hybrid, 40−74 20,884 134.2 91.0 126.1 159.4 92.5 64.8 109.3 (64.8−159.4)
Annual, 50−74 21,318 127.0§ 84.1§ 111.4§ 113.2§ 87.5§ 62.4§ 99.5 (62.4−127.0)§
Annual, 45−74 26,136 138.9 97.3 129.5 129.4§ 99.5 71.7 114.5 (71.7−138.9)
Annual, 40−74 31,037 146.6 107.3 137.2 160.6 107.6 80.0 122.4 (80.0−160.6)

D = Dana-Farber Cancer Institute; E = Erasmus Medical Center; GE = Georgetown University Medical Center and Albert Einstein College of Medicine; M = MD Anderson Cancer Center; QALY = quality-adjusted life-year; S = Stanford University; W = University of Wisconsin and Harvard Medical School.
* 100% of women receive adjuvant systemic therapy based on recommended stage and estrogen receptor/human epidermal growth factor-2 receptor–specific adjuvant therapy, and age (i.e., ER+ women less than 50 years were assigned tamoxifen, and ER + women 50 years and older were assigned tamoxifen or an aromatase inhibitor).
Strategies are ranked from the least to the most mammograms, where the number of mammographies is the median across models. Not all possible mammographies in the age interval are obtained because some women die of other causes before screening would occur.
Without screening, the median probability of dying of breast cancer is 2.50% (range, 1.50%–3.20%). Thus, if a particular screening strategy leads to a 30% reduction in breast cancer mortality, the probability of breast cancer mortality was reduced from 2.50% to 1.75%. This translates into 7.5 deaths averted per 1000 women screened. Table 3 includes the absolute reduction in breast cancer deaths (i.e., deaths averted) versus no screening for each strategy.
§ Strategies that are inferior or inefficient ("dominated") within a specific model; a strategy is classified as such if another strategy results in an equal or higher benefit (percentage of decline in mortality, life-years gained, or QALYs) with fewer harms (e.g., average screening examinations).
ǁ Adjusted for general health, diagnosis, screening, and treatment.

Table 2. Incremental Changes in Breast Cancer Deaths Averted, by Interval, Age of Screening Initiation, and Model*

Model Breast Cancer Deaths Averted per 1000 Women, n (Breast Cancer Mortality Reduction, %)
Annual Screening Biennial Screening
Start at Age 40 vs. 50 y Start at Age 45 vs. 50 y Start at Age 40 vs. 50 y Start at Age 45 vs. 50 y
D 1.1 (3.4) 0.6 (2.1) 0.9 (2.7) 0.3 (1.0)
E 1.5 (6.2) 0.9 (3.6) 1.0 (4.3) 0.4 (1.6)
GE 1.5 (6.0) 1.0 (4.0) 1.0 (4.1) 0.5 (2.2)
M 1.7 (5.3) 0.7 (2.3) 1.7 (5.1) 0.5 (1.6)
S 1.1 (5.2) 0.7 (3.1) 0.9 (4.1) 0.4 (1.7)
W 1.1 (7.3) 0.6 (3.8) 0.8 (5.1) 0.2 (1.3)
Median 1.3 (5.7) 0.7 (3.4) 1.0 (4.2) 0.4 (1.6)

D = Dana-Farber Cancer Institute; E = Erasmus Medical Center; GE = Georgetown University Medical Center and Albert Einstein College of Medicine; M = MD Anderson Cancer Center; S = Stanford University; W = University of Wisconsin and Harvard Medical School.
* Incremental difference between starting at age 40 or 45 years versus 50 years. Annual is comparing 40–74 (or 45–74) with 50–74; biennial is comparing 40–74 (or 45–74) with 50–74. Hybrid strategies are compared with 50–74 y; therefore, for those incremental comparisons, the hybrid results are the same as the annual results and are not shown separately here.

Table 3. Lifetime Benefits and Harms of Screening Strategies, Based on Starting Ages and Screening Intervals

Strategy
and
Age
Group
Median Value (Range Across Models) per 1000 Women Screened vs No Screening*
Screens, n Breast Cancer
Deaths Averted, n
False-Positive
Screens, n
Benign Breast
Biopsies, n
Overdiagnosed Cases
(Invasive and DCIS), n
All Overdiagnosed
Cases, %
Biennial
50−74 11,127 7 (4–9) 953 (830–1325) 146 (121–205) 19 (11–34) 12 (8–22)
45−74 13,212 8 (4–9) 1220 (930–1599) 176 (131–232) 19 (11–34) 12 (8–22)
40−74 16,013 8 (5–10) 1529 (1100–1976) 213 (153–276) 21 (12–38) 13 (9–24)
Hybrid
45−74 15,966 8 (5–9) 1520 (1160–1968) 202 (154–266) 21 (12–40) 13 (8–25)
40−74 20,884 9 (5–10) 2106 (1480–2623) 256 (184–325) 23 (12–44) 14 (9–27)
Annual
50−74 21,318 9 (5–10) 1798 (1706–2445) 228 (219–317) 25 (12–68) 15 (8–36)
45−74 26,136 9 (6–11) 2355 (2185–3087) 283 (265–376) 28 (12–74) 17 (9–38)
40−74 31,037 10 (6–11) 2941 (2550–3742) 338 (296–435) 30 (13–77) 18 (9–39)

* In all scenarios, 100% of women receive adjuvant systemic therapy based on recommended stage and ER/HER2-specific adjuvant therapy and age (ER + women under age 50 received tamoxifen and ER+ women 50 years and older received either tamoxifen or aromatase inhibitors.
Overdiagnosed cases are those that would not have been clinically detected in the absence of screening (i.e., cases in which the patient does not die of breast cancer owing to lack of progressive potential or death from a competing non–breast cancer cause). The result includes overdiagnosis of ductal carcinoma in situ (DCIS) and invasive disease. Overdiagnosis is calculated by comparing cases detected in the screening scenario with those detected in the nonscreened scenario. Model S (Stanford University) is excluded because it does not include DCIS. The percentage of overdiagnosis is calculated as the proportion of all cases detected in the screening strategy that are overdiagnosis.
The upper range for all estimates of overdiagnosis is based on results from model M (MD Anderson Cancer Center). Model M generates very high overdiagnosis on the basis of the assumption that incidence in the absence of screening has essentially remained flat since 1975–1979, with almost all of the increases over time attributable to screening. The other models use some form of an age–period–cohort model for incidence in the absence of screening, where some of the increases in incidence are due to screening and some to changes in risk factors (e.g., use of hormone replacement therapy), generating lower rates of overdiagnosis. Other sources of variation across models are related to assumptions about the proportions of DCIS cases that never progress to invasive cancer or the number of early invasive cancers that might be nonprogressive. In general, models that assume higher proportions of DCIS or invasive cancer to be nonprogressive generate higher estimates of overdiagnosis than models that assume less nonprogressive disease. The underlying incidence in the absence of screening and the proportion and types of tumors that are nonprogressive are unknown and unobservable; therefore, the different results across models based on their respective assumptions provide a range of possible overdiagnosis.

Figure. Efficiency frontier for life-years gained versus mammograms performed per 1000 women in model D (Dana-Farber Cancer Institute).

Text Description is shown below.

Appendix Figure 2 shows efficiency frontier graphs for all 6 models. The graph plotted the average gain in life-years per additional mammogram performed per 1000 women for each screening strategy (vs. no screening). Biennial strategies are indicated with a square; hybrid strategies (annual in the 40s followed by biennial from 50 to 74 years of age) with a triangle; and annual strategies with a circle. Efficient strategies were plotted (i.e., those in which increases in mammography use resulted in greater life-years gained than the next less intensive strategy). The line represents the “efficiency frontier” by joining efficient strategies in which increases in mammography use resulted in greater life-years gained than the next less intensive efficient strategy. Strategies on this line would be considered efficient because they achieve the greatest gain in benefit (life-years gained) per harm or use of mammograms. Strategies that use more mammograms but still have small benefits (i.e., a shallower slope than the next best strategy) are considered to be less efficient (i.e., weakly dominated). When and if the slope in the efficiency frontier plot levels off, it means that the additional life-years gained per increase in mammography are small relative to the previous strategies and could indicate a point at which additional screening might be considered as having a low return (or additional benefit). There is no definitive inflection point across the models for the strategies or metrics evaluated. Black strategies are efficient; gray strategies close to the efficiency frontier are less efficient; and open gray strategies are inefficient (inferior, or dominated). Reference[[33 provides efficiency frontiers for other harm and benefit metrics.

Appendix Table 1. Utility Input Parameter Values

State Utilities for Cancer-Related States*
Utility Disutility
(Worst Case 150%, 200%)
Duration Unit
Cancer treatment for local or DCIS 0.9 0.1 (0.15, 0.20) 2 Year
Cancer treatment for regional 0.75 0.25 (0.375, 0.50) 2 Year
Cancer treatment for distant 0.6 0.4 (0.6, 0.8) Until death -
Screening attendance (routine screening) 0.994 0.006 (0.009, 0.012) 1 Week
Diagnostic phase (evaluation of positive screen) 0.895 0.105 (0.158, 0.210) 5 Weeks
Age-Specific Utilities for General Health in US Women
Age Healthy Base Value (range)
20y 0.913 (0.905–0.920)
25y 0.913 (0.905–0.920)
30y 0.893 (0.886–0.900)
35y 0.893 (0.886–0.900)
40y 0.863 (0.855–0.871)
45y 0.863 (0.855–0.871)
50y 0.837 (0.829–0.846)
55y 0.837 (0.829–0.846)
60y 0.811 (0.800–0.822)
65y 0.811 (0.800–0.822)
70y 0.771 (0.758–0.784)
75y 0.771 (0.758–0.784)
80y 0.724 (0.701–0.747)
85y 0.724 (0.701–0.747)

DCIS = ductal carcinoma in situ.
* From references40, 41
Values from the EuroQoL-5D quality-of-life questionnaire.39

Appendix Figure 1. Modeled versus observed incidence of breast cancer and breast cancer–specific mortality in women aged 40 to 100 years.

Text Description is shown below image.

Top. Incidence of invasive disease.
Middle*. Incidence of invasive disease and ductal carcinoma in situ.
Bottom. Breast cancer–specific mortality.
The models closely estimate observed U.S. trends in incidence and breast cancer–specific mortality. Using inputs for actual dissemination of screening and treatment in the United States, the models all captured the major trends in incidence over time. Early increases with the advent of mammography in the mid-1980s are seen, followed by a downturn in the 2000s and then a leveling off. The models also captured the general shape of decreases in breast cancer–specific mortality over time. All models show an increase in incidence with the introduction of mammography screening. Model GE has a steep peak in incidence in 2005 owing to the specific method for capturing the transition from plain film to digital mammography, because digital mammography has higher sensitivity and detection of ductal carcinoma in situ than plain film mammography; other models include a more gradual transition surrounding this period.
D = Dana-Farber Cancer Institute; E = Erasmus Medical Center; GE = Georgetown University Medical Center and Albert Einstein College of Medicine; M = MD Anderson Cancer Center; QALY = quality-adjusted life-year; S = Stanford University; SEER = Surveillance, Epidemiology, and End Results; W = University of Wisconsin and Harvard Medical School.
* Model S does not include ductal carcinoma in situ.

Appendix Table 2. Approximation of the Age Trial With 13-y Follow-up, by Model*

Model Relative Risk for Breast Cancer
Death With 100% Screening
D 0.75
E 0.73
GE 0.65
M 0.72
S 0.69
W 0.71
Median (range) 0.72 (0.65–0.75)

Georgetown University Medical Center and Albert Einstein College of Medicine; M = MD Anderson Cancer Center; S = Stanford University; W = University of Wisconsin and Harvard Medical School.
* Projection of relative risk of breast cancer death with annual screening from age 40 to 49 y; biennial at age 50 and 52 y versus a control group with biennial screening at age 50 and 52 y. Because the models are estimating mortality reduction with actual screening, model estimates are most comparable to the Age trial results6 among women who actually attended screening. Model results show more benefit than observed in the trial because the models assume that 100% of women complied with the trial-specified screening schedule. In reality, not all women who were invited attended screening, and among those who attended, many did not attend all scheduled screening rounds. In addition, the models assumed 100% receipt of the most effective treatments.
Age trial invitation results (intention to treat): relative risk, 0.83 (95% CI, 0.66–1.04). Age trial results for women who actually were screened: relative risk, 0.76 (CI, 0.51–1.01).

Appendix Table 3. Annual Mortality Reduction Maintained by Biennial Screening, by Strategy and Model

Age at Screening Mortality Reduction, %
Model D Model E Model GE Model M* Model S Model W Median
50–74 79.8 76.7 84.6 98.9 82.8 72.0 81.3
45–74 77.8 73.4 81.5 96.6 80.2 68.3 79.0
40–74§ 79.7 75.6 82.3 98.2 82.0 71.6 80.8

D = Dana-Farber Cancer Institute; E = Erasmus Medical Center; GE = Georgetown University Medical Center and Albert Einstein College of Medicine; M = MD Anderson Cancer Center; S = Stanford University; W = University of Wisconsin and Harvard Medical School.
* Model M does not include a natural history component. On the basis of a combination of assumptions about underlying incidence trends in the absence of screening, it essentially yields a long lead time for invasive cancer; thus, all cancers found with annual screening can also be detected with biennial screening.
Percentage of reduction with annual screening in women aged 50–74 y that is maintained by biennial screening in women aged 50–74 y is calculated as the percent mortality reduction with biennial screening in women aged 50–74 y divided by the percent mortality reduction with annual screening in women aged 50–74 y.
Percentage of reduction with annual screening in women aged 45–74 y that is maintained by biennial screening in women aged 45–74 y is calculated as the percent mortality reduction with biennial screening in women aged 45–74 y divided by the percent mortality reduction with annual screening in women aged 45–74 y.
§ Percentage of reduction with annual screening in women aged 40–74 y that is maintained by biennial screening in women aged 40–74 y is calculated as the percent mortality reduction with biennial screening in women aged 40–74 y divided by the percent mortality reduction with annual screening in women aged 40–74 y.

Appendix Figure 2. Efficiency frontier for life-years gained versus mammograms performed for each screening strategy, by model.

Text Description is shown below image.

The average gain in life-years per additional mammogram performed per 1000 women for each screening strategy (vs. no screening). Biennial strategies are indicated with a square; hybrid strategies (annual in the 40s followed by biennial from 50 to 74 years of age) with a triangle; and annual strategies with a circle. Efficient strategies were plotted (those in which increases in mammography use resulted in greater life-years gained than the next least-intensive strategy). The line represents the “efficiency frontier” by joining efficient strategies in which increases in mammography use resulted in greater life-years gained than the next less intensive efficient strategy. Strategies on this line would be considered efficient because they achieve the greatest gain in benefit (life years gained) per harm or use of mammograms. Strategies that use more mammograms but still have small benefits (i.e., a shallower slope than the next best strategy) are considered to be less efficient (i.e., weakly dominated). When and if the slope in the efficiency frontier plot levels off, it means that the additional life-years gained per increase in mammography are small relative to the previous strategies and could indicate a point at which additional screening might be considered as having a low return (or additional benefit). There is no definitive inflection point across the models for the strategies or metrics evaluated. Black strategies are efficient; gray strategies close to the efficiency frontier are less efficient; and open gray strategies are inefficient (inferior, or dominated). Reference 33 provides efficiency frontiers for other harm and benefit metrics.
D = Dana-Farber Cancer Institute; E = Erasmus Medical Center; GE = Georgetown University Medical Center and Albert Einstein College of Medicine; M = MD Anderson Cancer Center; QALY = quality-adjusted life-year; S = Stanford University; W = University of Wisconsin and Harvard Medical School.

Current as of: January 2016

Internet Citation: Evidence Summary: Collaborative Modeling of U.S. Breast Cancer Screening Strategies: Breast Cancer: Screening. U.S. Preventive Services Task Force. August 2016.
https://www.uspreventiveservicestaskforce.org/Page/Document/evidence-summary-collaborative-modeling-of-us-breast-cancer-/breast-cancer-screening1

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