The Nationwide Inpatient Sample (NIS) of the Healthcare Cost and Utilization Project (HCUP) was established to provide analyses of hospital utilization across the United States. The target universe includes all acute-care discharges from all community hospitals in the United States; the NIS comprises all discharges from a sample of hospitals in this target universe.
NIS Release | Calendar Year | States | Sample Hospitals | Sample Discharge (millions) |
---|---|---|---|---|
1 | 1988–1992 | 8–11 | 758–875 | 5.2–6.2 |
2 | 1993 | 17 | 913 | 6.5 |
3 | 1994 | 17 | 904 | 6.4 |
4 | 1995 | 19 | 938 | 6.7 |
5 | 1996 | 19 | 906 | 6.5 |
6 | 1997 | 22 | 1012 | 7.1 |
Thus, the NIS supports both cross-sectional and longitudinal analyses.
Potential research issues focus on both discharge- and hospital-level outcomes. Discharge outcomes of interest include trends in inpatient treatments with respect to:
Hospital outcomes of interest include:
These and other outcomes are of interest for the nation as a whole and for policy-relevant inpatient subgroups defined by geographic regions, patient demographics, hospital characteristics, physician characteristics, and pay sources.
This report provides a detailed description of the NIS, Release 6 sample design, as well as a summary of the resultant hospital sample. Sample weights were developed to obtain national estimates of hospital and inpatient parameters. These weights and other special-use weights are described in detail. Tables include cumulative information for all six NIS releases to provide a longitudinal view of the database.
The hospital universe is defined by all hospitals that were open during any part of the calendar year and were designated as community hospitals in the American Hospital Association (AHA) Annual Survey of Hospitals. For purposes of the NIS, the definition of a community hospital is that used by the AHA: "all nonfederal short-term general and other specialty hospitals, excluding hospital units of institutions." Consequently, Veterans Hospitals and other federal hospitals are excluded. Table 1 shows the number of universe hospitals for each year based on the AHA Annual Survey.
Year | Number of Hospitals |
---|---|
1988 | 5,607 |
1989 | 5,548 |
1990 | 5,468 |
1991 | 5,412 |
1992 | 5,334 |
1993 | 5,313 |
1994 | 5,290 |
1995 | 5,260 |
1996 | 5,182 |
1997 | 5,113 |
All hospital entities that were designated community hospitals in the AHA hospital file were included in the hospital universe. Therefore, if two or more community hospitals merged to create a new community hospital, the original hospitals and the newly-formed hospital were all considered separate hospital entities in the universe for the year of the merge. Likewise, if a community hospital split, the original hospital and all newly created community hospitals were separate entities in the universe for the year of the split. Finally, community hospitals that closed during a year were included as long as they were in operation during some part of the calendar year.
To help ensure representativeness, sampling strata were defined based on five hospital characteristics contained in the AHA hospital files. The stratification variables were as follows:
Location and Teaching Status | Hospital Bed Size | ||
---|---|---|---|
Small | Medium | Large | |
Rural | 1-49 | 50-99 | 100+ |
Urban, non-teaching | 1-99 | 100-199 | 200+ |
Urban, teaching | 1-299 | 300-499 | 500+ |
Rural hospitals were not split according to teaching status, because rural teaching hospitals were rare. For example, in 1988 there were only 20 rural teaching hospitals. The bedsize categories were defined within location and teaching status because they would otherwise have been redundant. Rural hospitals tend to be small; urban nonteaching hospitals tend to be medium-sized; and urban teaching hospitals tend to be large. Yet it was important to recognize gradations of size within these types of hospitals.
For example, in serving rural discharges, the role of "large" rural hospitals (particularly rural referral centers) often differs from the role of "small" rural hospitals. The cut-off points for the bedsize categories are consistent with those used in Hospital Statistics, published annually by the AHA.
To further ensure geographic representativeness, implicit stratification variables included state and three-digit zip code (the first three digits of the hospital's five-digit zip code). The hospitals were sorted according to these variables prior to systematic sampling.
For each year, the universe of hospitals was established as all community hospitals located in the U.S. However, it was not feasible to obtain and process all-payer discharge data from a random sample of the entire universe of hospitals for at least two reasons. First, all-payer discharge data were not available from all hospitals for research purposes. Second, based on the experience of prior hospital discharge data collections, it would have been too costly to obtain data from individual hospitals, and it would have been too burdensome to process each hospital's unique data structure.
Therefore, the NIS sampling frame was constructed from the subset of universe hospitals that released their discharge data for research use. Two sources for all-payer discharge data were state agencies and private data organizations, primarily state hospital associations. At the time when the sample was drawn, the Agency for Health Care Policy and Research (AHCPR) had agreements with 22 data sources that maintain statewide, all-payer discharge data files to include their data in the HCUP database. However, only 8 states in 1988 and 11 states in 1989-1992 could be included in the first release of the NIS, an additional 6 states were included in the second and the third release of the NIS, another 2 states were included in the fourth and the fifth releases of the NIS, and 3 more states were included in this sixth release of the NIS as shown in Table 3.
Years | States in the Frame |
---|---|
NIS, Release 1 | |
1988 | California, Colorado, Florida, Iowa, Illinois, Massachusetts, New Jersey, and Washington |
1989-1992 | Add Arizona, Pennsylvania, and Wisconsin |
NIS, Release 2 | |
1993 | Add Connecticut, Kansas, Maryland, New York, Oregon, South Carolina |
NIS, Release 3 | |
1994 | No new additions |
NIS, Release 4 | |
1995 | Add Missouri, Tennessee |
NIS, Release 5 | |
1996 | No new additions |
NIS, Release 6 | |
1997 | Add Georgia, Hawaii, and Utah |
The list of the entire frame of hospitals was composed of all AHA community hospitals in each of the frame states that could be matched to the discharge data provided to HCUP. If an AHA community hospital could not be matched to the discharge data provided by the data source, it was eliminated from the sampling frame (but not from the target universe). Further restrictions were put on the sampling frames for Georgia, Hawaii, Illinois, South Carolina, Missouri, and Tennessee.
The Illinois Health Care Cost Containment Council stipulated that no more than 40 percent of the discharges provided by Illinois could be included in the database for any calendar quarter. Consequently, a systematic random sample of Illinois hospitals was drawn for the 1997 frame. This prevented the sample from including more than 40 percent of Illinois discharges.
Georgia, Hawaii, South Carolina and Tennessee stipulated that only hospitals that appear in sampling strata with two or more hospitals were to be included in the NIS.
Due to this restriction, one Georgia hospital, six Hawaii hospitals, six South Carolina hospitals and five Tennessee hospitals were excluded from the 1997 frame leaving 158 Georgia community hospitals, 11 Hawaii hospitals, 54 South Carolina hospitals and 92 Tennessee community hospitals in the 1997 frame.
Missouri stipulated that only hospitals that had signed releases for public use should be included in the NIS. For 1997, thirty-five Missouri hospitals signed releases for confidential use only. These hospitals were excluded from the sampling frame, leaving 75 hospitals in the 1997 frame.
The number of frame hospitals for each year is shown in Table 4.
Year | Number of Hospitals |
---|---|
1988 | 1,247 |
1989 | 1,658 |
1990 | 1,620 |
1991 | 1,604 |
1992 | 1,591 |
1993 | 2,168 |
1994 | 2,135 |
1995 | 2,284 |
1996 | 2,268 |
1997 | 2,452 |
The NIS is a stratified probability sample of hospitals in the frame, with sampling probabilities calculated to select 20 percent of the universe contained in each stratum. The overall objective was to select a sample of hospitals "generalizable" to the target universe, which includes hospitals outside the frame (zero probability of selection). Moreover, this sample was to be geographically dispersed, yet drawn from the subset of states with inpatient discharge data that agreed to provide such data to the project.
It should be possible, for example, to estimate DRG-specific average lengths of stay over all U.S. hospitals using weighted average lengths of stay, based on averages or regression estimates from the NIS. Ideally, relationships among outcomes and their correlates estimated from the NIS should generally hold across all U.S. hospitals. However, since only 22 states contributed data to this sixth release, some estimates may differ from estimates from comparative data sources. When possible, estimates based on the NIS should be checked against national benchmarks, such as Medicare data or data from the National Hospital Discharge Survey to determine the appropriateness of the NIS for specific analyses (see the Technical Supplement: Comparative Analysis of HCUP and NHDS Inpatient Discharge Data).
The target sample size was 20 percent of the total number of community hospitals in the U.S. for 1997. This sample size was determined by AHCPR based on their experience with similar research databases.
Alternative stratified sampling allocation schemes were considered. However, allocation proportional to the number of hospitals is preferred for several reasons:
Once the universe of hospitals was stratified, up to 20 percent of the total number of U.S. hospitals was randomly selected within each stratum. If too few frame hospitals were in the stratum, then all frame hospitals were selected for the NIS, subject to sampling restrictions specified by states. To simplify variance calculations, at least two hospitals were drawn from each stratum. If fewer than two frame hospitals were contained in a stratum, then that stratum was merged with an "adjacent" stratum containing hospitals with similar characteristics.
A systematic random sample was drawn from each stratum, after sorting hospitals by state within each stratum, then by the three-digit zip code (the first three digits of the hospital's five-digit zip code) within each state, and then by a random number within each three-digit zip code. These sorts ensured further geographic generalizability of hospitals within the frame states, and random ordering of hospitals within three-digit zip codes.
Generally, three-digit zip codes that are near in value are geographically near within a state. Furthermore, the U.S. Postal Service locates regional mail distribution centers at the three-digit level. Thus, the boundaries tend to be a compromise between geographic size and population size.
The 1997 sample was drawn by a procedure that retained most of the 1995 hospitals while allowing hospitals new to the frame an opportunity to enter the 1997 NIS. (Note: The 1996 NIS was not selected through a sampling procedure but was constructed as the subset of 1995 NIS hospitals that continued to supply data in 1996).
Even in frame states that were present in the 1995 sample, hospitals that opened in 1997 needed a chance to enter the sample. Also, hospitals that changed strata between 1995 and 1997 were considered new to the 1997 frame.
Consequently, a recursive procedure was developed to update the sample from year to year in a way that properly accounted for changes in stratum size, composition, and sampling rate. The goal of this procedure was to maximize the year-to-year overlap among sample hospitals, yet keep the sampling rate constant for all hospitals within a stratum.
The following procedure provides rules for creating a "year 2" sample, given that a "year 1" sample had already been drawn. In this example, year 1 would be 1995 and year 2 would be 1997. All notation is assumed to refer to sizes and probabilities within a particular stratum.
Probabilities P_{1} and P_{2} were calculated for sampling hospitals from the frame within the stratum for year 1 and year 2, respectively, based on the frame and universe for year 1 and year 2, respectively. These probabilities were set by the same algorithm used to calculate P for the original (1988) hospital sample (see Technical Supplement: Design of the HCUP Nationwide Inpatient Sample, Release 1, section "1988 NIS Hospital Sampling Procedure.")
Now consider the three possibilities associated with changes between years 1 and 2 in the stratum-specific hospital sampling probabilities:
Below is the procedure used for each of these three cases with one exception: if the stratum-specific probability of selection P_{2} was equal to 1, then all frame hospitals were selected for the year 2 sample, regardless of the value of P_{1}.
If the probability P_{2} was the same as P_{1}, all hospitals in the year 1 sample that remained in the year 2 frame were retained for the year 2 sample. Any new frame hospitals (those in the year 2 frame but not in the year 1 frame) were selected at the rate P_{2}, using the systematic sampling method described for the 1988 sample selection in Technical Supplement: Design of the HCUP Nationwide Inpatient Sample, Release 1.
Now consider the case where the probability of selection decreased between years 1 and 2. First, hospitals new to the frame were sampled with probability P_{2}. Second, hospitals previously selected for the year 1 sample (that remained in the year 2 frame) were selected for the year 2 sample with probability P_{2} ÷ P_{1}.
The justification for this second procedure was straightforward. For the year 1 sample hospitals that stayed in the frame, the year 1 sample was viewed as the first stage of a two-stage sampling process. The first stage was carried out at the sampling rate of P_{1}. The second stage was carried out at the sampling rate of P_{2} ÷ P_{1}. Consequently, the "overall" probability of selection was P_{1} x P_{2} ÷ P_{1} = P_{2}.
The procedures associated with the case in which the probability of selection was increased between year 1 and year 2 were equally straightforward. First, hospitals new to the frame were sampled with probability P_{2}. Second, hospitals that were selected in year 1 (that remained in the year 2 frame) were selected for the year 2 sample. Third, hospitals that were in the frame for both years 1 and 2, but not selected for the year 1 sample, were selected for the year 2 sample with probability (P_{2}-P_{1}) ÷ (1-P_{1}).
The justification for this sampling rate, (P_{2}-P_{1}) ÷ (1-P_{1}), is somewhat complex. In year 1 certain frame hospitals were included in the sample at the rate P_{1}. This can also be viewed as having excluded a set of hospitals at the rate (1-P_{1}). Likewise, in year 2 it was imperative that each hospital excluded from the year 1 sample be excluded from the year 2 sample at an overall rate of (1-P_{2}).
Since P_{2} > P_{1}, then (1-P_{2}) < (1-P_{1}). Therefore, just as was done for the case of P_{2} < P_{1}, multistage selection was implemented. However, it was implemented for exclusion rather than inclusion.
Therefore, those hospitals excluded from the year 1 sample were also excluded from the year 2 sample at the rate S = (1-P_{2}) ÷ (1-P_{1}). This gave them the desired overall exclusion rate of (1-P_{1}) x (1-P_{2}) ÷ (1-P_{1}) = (1-P_{2}). Consequently, the inclusion rate for these hospitals was set at 1-S = (P_{2}-P_{1}) ÷ (1-P_{1}).
Beginning in 1993, the NIS samples contain no zero-weight hospitals. For a description of zero-weight hospitals in the 1988-1992 sample, see the Technical Supplement: Design of the HCUP Nationwide Inpatient Sample, Release 1.
Two nonoverlapping 10 percent subsamples of discharges were drawn from the NIS file for each year. The subsamples were selected by drawing every tenth discharge starting with two different starting points (randomly selected between 1 and 10). Having a different starting point for each of the two subsamples guaranteed that they would not overlap. Discharges were sampled so that 10 percent of each hospital's discharges in each quarter were selected for each of the subsamples. The two samples can be combined to form a single, generalizable 20 percent subsample of discharges.
The annual numbers of hospitals and discharges in each release of the NIS are shown in Table 5 for both the regular NIS sample and the total sample (which includes zero-weight hospitals for 1988-1992).
Regular Sample | Total Sample | |||
---|---|---|---|---|
Year | Number of Hospitals | Number of Discharges | Number of Hospitals | Number of Discharges |
NIS, Release 1 | ||||
1988 | 758 | 5,242,904 | 759 | 5,265,756 |
1989 | 875 | 6,067,667 | 882 | 6,110,064 |
1990 | 861 | 6,156,638 | 871 | 6,268,515 |
1991 | 847 | 5,984,270 | 859 | 6,156,188 |
1992 | 838 | 6,008,001 | 856 | 6,195,744 |
NIS, Release 2 | ||||
1993 | 913 | 6,538,976 | 913 | 6,538,976 |
NIS, Release 3 | ||||
1994 | 904 | 6,385,011 | 904 | 6,385,011 |
NIS, Release 4 | ||||
1995 | 938 | 6,714,935 | 938 | 6,714,935 |
NIS, Release 5 | ||||
1996 | 906 | 6,542,069 | 906 | 6,542,069 |
NIS, Release 6 | ||||
1997 | 1,012 | 7,148,420 | 1,012 | 7,148,420 |
Total | 62,788,891 | 63,325,678 |
A more detailed breakdown of the 1997 NIS hospital sample by geographic region is shown in Table 6. For each geographic region, Table 6 shows the number of:
Region | Universe | Frame | Sample | Target | Shortfall |
---|---|---|---|---|---|
NE | 737 | 616 | 154 | 147 | 7 |
MW | 1,453 | 546 | 302 | 291 | 11 |
S | 1,968 | 553 | 365 | 394 | -29 |
W | 955 | 737 | 191 | 191 | 0 |
Total | 5,113 | 2,452 | 1,012 | 1,023 | -11 |
For example, in 1997 the Northeast region contained 737 hospitals in the universe. It also contained 616 hospitals in the frame, of which 154 hospitals were drawn for the sample. This was seven hospitals more than the target sample size of 147.
Table 0 shows the number of hospitals in the universe, frame, and regular sample for each state in the sampling frame for 1997. The difference between the universe and the frame represents the difference in the number of community hospitals in the 1997 AHA Annual Survey of Hospitals and the number of community hospitals for which data were supplied to HCUP in all states except Georgia, Hawaii, Illinois, South Carolina, Tennessee and Missouri.
The number of hospitals in the NIS hospital samples that continue across multiple sample years is shown in Table 7. This table will be of interest to those who may combine Releases 1 through 6 of the NIS. Table 8 shows that longitudinal cohorts that span several years and include 1988 and 1993 are the lowest in number of continuing sample hospitals. For example, if 1988 is taken as a starting year, only 30.7 percent of the 1988 hospital sample continued in the 1997 sample (233 of 758).
State | Universe | Frame | Sample |
---|---|---|---|
AZ | 64 | 62 | 14 |
CA | 415 | 411 | 107 |
CO | 67 | 66 | 18 |
CT | 34 | 32 | 9 |
FL | 210 | 198 | 117 |
GA | 159 | 158 | 115 |
HI | 20 | 11 | 3 |
IA | 115 | 115 | 52 |
IL | 203 | 112 | 73 |
KS | 131 | 120 | 62 |
MA | 84 | 73 | 18 |
MD | 51 | 51 | 35 |
MO | 125 | 75 | 44 |
NJ | 85 | 78 | 19 |
NY | 225 | 222 | 56 |
OR | 61 | 59 | 16 |
PA | 217 | 211 | 52 |
SC | 65 | 54 | 34 |
TN | 126 | 92 | 64 |
UT | 41 | 40 | 13 |
WA | 89 | 88 | 20 |
WI | 124 | 124 | 71 |
TOTAL | 2,711 | 2,452 | 1,012 |
Number of Years | Calendar Years | Longitudinal Regular Sample Hospitals | % of Base Year Sample | Longitudinal Regular Sample Discharges |
---|---|---|---|---|
2 | 1988-1989 | 610 | 80.5 | 8,492,039 |
1989-1990 | 815 | 93.1 | 11,525,749 | |
1990-1991 | 802 | 93.1 | 11,297,175 | |
1991-1992 | 781 | 92.2 | 11,272,981 | |
1992-1993 | 609 | 72.7 | 8,804,638 | |
1993-1994 | 693 | 75.9 | 10,271,404 | |
1994-1995 | 762 | 84.3 | 10,747,682 | |
1995-1996 | 906 | 96.6 | 13,050,676 | |
1996-1997 | 741 | 81.8 | 10,743,200 | |
3 | 1988-1990 | 573 | 75.6 | 12,168,677 |
1989-1991 | 763 | 87.2 | 16,074,381 | |
1990-1992 | 745 | 86.5 | 16,085,651 | |
1991-1993 | 570 | 67.3 | 12,559,421 | |
1992-1994 | 540 | 64.4 | 11,279,667 | |
1993-1995 | 598 | 65.5 | 13,241,070 | |
1994-1996 | 740 | 81.9 | 15,651,230 | |
1995-1997 | 741 | 79.0 | 16,058,401 | |
4 | 1988-1991 | 542 | 71.5 | 15,096,807 |
1989-1992 | 709 | 81.0 | 20,340,970 | |
1990-1993 | 548 | 63.6 | 16,023,500 | |
1991-1994 | 508 | 60.0 | 14,481,319 | |
1992-1995 | 464 | 55.4 | 12,712,613 | |
1993-1996 | 583 | 63.9 | 17,203,387 | |
1994-1997 | 617 | 68.3 | 17,490,946 | |
5 | 1988-1992 | 502 | 66.2 | 18,106,098 |
1989-1993 | 523 | 59.8 | 19,000,777 | |
1990-1994 | 490 | 56.9 | 17,437,229 | |
1991-1995 | 439 | 51.8 | 15,405,253 | |
1992-1996 | 453 | 54.1 | 15,509,564 | |
1993-1997 | 485 | 53.1 | 17,972,148 | |
6 | 1988-1993 | 378 | 49.9 | 16,906,818 |
1989-1994 | 471 | 53.8 | 19,987,910 | |
1990-1995 | 422 | 49.0 | 14,817,797 | |
1991-1996 | 429 | 50.6 | 18,041,571 | |
1992-1997 | 379 | 45.2 | 15,670,244 | |
7 | 1988-1994 | 335 | 44.2 | 17,128,064 |
1989-1995 | 408 | 46.6 | 19,924,107 | |
1990-1996 | 413 | 48.0 | 20,293,152 | |
1991-1997 | 359 | 42.4 | 17,776,471 | |
8 | 1988-1995 | 289 | 38.1 | 16,658,485 |
1989-1996 | 400 | 45.7 | 22,403,308 | |
1990-1997 | 344 | 40.0 | 19,488,725 | |
9 | 1988-1996 | 283 | 37.3 | 18,576,353 |
1989-1997 | 334 | 38.2 | 21,183,992 | |
10 | 1988-1997 | 223 | 30.7 | 17,411,298 |
Although the sampling design was simple and straightforward, it is necessary to incorporate sample weights to obtain state and national estimates. Therefore, sample weights were developed separately for hospital- and discharge-level analyses. Three hospital-level weights were developed to weight NIS sample hospitals to the state, frame, and universe. Similarly, three discharge-level weights were developed to weight NIS sample discharges to the state, frame, and universe.
Hospital weights to the universe were calculated by post-stratification. For each year, hospitals were stratified on the same variables that were used for sampling: geographic region, urban/rural location, teaching status, bedsize, and control. The strata that were collapsed for sampling were also collapsed for sample weight calculations. Within stratum s, each NIS sample hospital's universe weight was calculated as:
W_{s}(universe) = N_{s}(universe) ÷ N_{s}(sample),
where N_{s}(universe) and N_{s}(sample) were the number of community hospitals within stratum s in the universe and sample, respectively. Thus, each hospital's universe weight is equal to the number of universe hospitals it represented during that year.
Hospital-level sampling weights were also calculated to represent the entire collection of states in the frame using the same post-stratification scheme as described above for the weights to represent the universe. For each year, within stratum s, each NIS sample hospital's frame weight was calculated as:
W_{s}(frame) = N_{s}(frame) ÷ N_{s}(sample).
N_{s}(frame) was the total number of universe community hospitals within stratum s in the states that contributed data to the frame. N_{s}(sample) was the number of sample hospitals selected for the NIS in stratum s. Thus, each hospital's frame weight is equal to the number of universe hospitals it represented in the frame states during that year.
For each year, a hospital's weight to its state was calculated in a similar fashion. Within each state, strata often had to be collapsed after sample selection for development of weights to ensure a minimum of two sample hospitals within each stratum. For each state and each year, within stratum s, each NIS sample hospital's state weight was calculated as:
W_{s}(state) = N_{s}(state) ÷ N_{s}(state sample).
N_{s}(state) was the number of universe community hospitals in the state within stratum s. N_{s}(state sample) was the number of hospitals selected for the NIS from that state in stratum s. Thus, each hospital's state weight is equal to the number of hospitals that it represented in its state during that year.
All of these hospital weights can be rescaled if necessary for selected analyses, to sum to the NIS hospital sample size each year.
The calculations for discharge-level sampling weights were very similar to the calculations of hospital-level sampling weights. The discharge weights usually are constant for all discharges within a stratum.
The only exceptions were for strata with sample hospitals that, according to the AHA files, were open for the entire year but contributed less than their full year of data to the NIS. For those hospitals, we adjusted the number of observed discharges by a factor 4 ÷ Q, where Q was the number of calendar quarters that the hospital contributed discharges to the NIS. For example, when a sample hospital contributed only two quarters of discharge data to the NIS, the adjusted number of discharges was double the observed number.
With that minor adjustment, each discharge weight is essentially equal to the number of reference (universe, frame, or state) discharges that each sampled discharge represented in its stratum. This calculation was possible because the number of total discharges was available for every hospital in the universe from the AHA files. Each universe hospital's AHA discharge total was calculated as the sum of newborns and total facility discharges.
Discharge weights to the universe were calculated by post-stratification. Hospitals were stratified just as they were for universe hospital weight calculations. Within stratum s, for hospital i, each NIS sample discharge's universe weight was calculated as:
DW_{is}(universe) = [DN_{s}(universe) ÷ ADN_{s}(sample)] * (4 ÷ Q_{i}),
where DN_{s}(universe) was the number of discharges from community hospitals in the universe within stratum s; ADN_{s}(sample) was the number of adjusted discharges from sample hospitals selected for the NIS; and Qi was the number of quarters of discharge data contributed by hospital i to the NIS (usually Q_{i} = 4). Thus, each discharge's weight is equal to the number of universe discharges it represented in stratum s during that year.
Discharge-level sampling weights were also calculated to represent all discharges from the entire collection of states in the frame using the same post-stratification scheme described above for the discharge weights to represent the universe. For each year, within stratum s, for hospital i, each NIS sample discharge's frame weight was calculated as:
W_{is}(frame) = [DN_{s}(frame) ÷ ADN_{s}(sample)] * (4 ÷ Q_{i}),
DN_{s}(frame) was the number of discharges from all community hospitals in the states that contributed to the frame within stratum s. ADN_{s}(sample) was the number of adjusted discharges from sample hospitals selected for the NIS in stratum s. Q^{i} was the number of quarters of discharge data contributed by hospital i to the NIS (usually Q_{i} = 4). Thus, each discharge's frame weight is equal to the number of discharges it represented in the frame states during that year.
A discharge's weight to its state was similarly calculated. Strata were collapsed in the same way as they were for the state hospital weights to ensure a minimum of two sample hospitals within each stratum. Within stratum s, for hospital i, each NIS sample discharge's state weight was calculated as:
W_{is}(state) = [DN_{s}(state) ÷ ADN_{s}(state sample)] * (4 ÷ Q_{i}),
DN_{s}(state) was the number of discharges from all community hospitals in the state within stratum s. ADN_{s}(state sample) was the adjusted number of discharges from hospitals selected for the NIS from that state in stratum s. Q^{i} was the number of quarters of discharge data contributed by hospital i to the NIS (usually Q_{i} = 4). Thus, each discharge's state weight is equal to the number of discharges that it represented in its state during that year.
All of these discharge weights can be rescaled if necessary for selected analyses, to sum to the NIS discharge sample size each year.
In the 10 percent subsamples, each discharge had a 10 percent chance of being drawn. Therefore, the discharge weights contained in the Hospital Weights file can be multiplied by 10 for each of the subsamples, or multiplied by 5 for the two subsamples combined.
It may be important for researchers to calculate a measure of precision for some estimates based on the NIS sample data. Variance estimates must take into account both the sampling design and the form of the statistic. The sampling design was a stratified, single-stage cluster sample. A stratified random sample of hospitals (clusters) were drawn and then all discharges were included from each selected hospital.
If hospitals inside the frame were similar to hospitals outside the frame, the sample hospitals can be treated as if they were randomly selected from the entire universe of hospitals within each stratum. Standard formulas for a stratified, single-stage cluster sampling without replacement could be used to calculate statistics and their variances in most applications.
A multitude of statistics can be estimated from the NIS data. Several computer programs are listed below that calculate statistics and their variances from sample survey data. Some of these programs use general methods of variance calculations (e.g., the jackknife and balanced half-sample replications) that take into account the sampling design. However, it may be desirable to calculate variances using formulas specifically developed for some statistics.
In most cases, computer programs are readily available to perform these calculations. For instance, OSIRIS IV, developed at the University of Michigan, and SUDAAN, developed at the Research Triangle Institute, do calculations for numerous statistics arising from the stratified, single-stage cluster sampling design. An example of using SUDAAN to calculate variances in the NIS is presented in Technical Supplement: Calculating Variances Using Data from the HCUP Nationwide Inpatient Sample.^{3}
These variance calculations are based on finite-sample theory, which is an appropriate method for obtaining cross-sectional, nationwide estimates of outcomes. According to finite-sample theory, the intent of the estimation process is to obtain estimates that are precise representations of the nationwide population at a specific point in time. In the context of the NIS, any estimates that attempt to accurately describe characteristics (such as expenditure and utilization patterns or hospital market factors) and interrelationships among characteristics of hospitals and discharges during a specific year from 1988 to 1997 should be governed by finite-sample theory.
Alternatively, in the study of hypothetical population outcomes not limited to a specific point in time, analysts may be less interested in specific characteristics from the finite population (and time period) from which the sample was drawn, than they are in hypothetical characteristics of a conceptual "superpopulation" from which any particular finite population in a given year might have been drawn. According to this superpopulation model, the nationwide population in a given year is only a snapshot in time of the possible interrelationships among hospital, market, and discharge characteristics. In a given year, all possible interactions between such characteristics may not have been observed, but analysts may wish to predict or simulate interrelationships that may occur in the future.
Under the finite-population model, the variances of estimates approach zero as the sampling fraction approaches one, since the population is defined at that point in time, and because the estimate is for a characteristic as it existed at the time of sampling. This is in contrast to the superpopulation model, which adopts a stochastic viewpoint rather than a deterministic viewpoint. That is, the nationwide population in a particular year is viewed as a random sample of some underlying superpopulation over time.
Different methods are used for calculating variances under the two sample theories. Under the superpopulation (stochastic) model, procedures (such as those described by Potthoff, Woodbury, and Manton^{4}) have been developed to draw inferences using weights from complex samples. In this context, the survey weights are not used to weight the sampled cases to the universe, because the universe is conceptually infinite in size. Instead, these weights are used to produce unbiased estimates of parameters that govern the superpopulation.
In summary, the choice of an appropriate method for calculating variances for nationwide estimates depends on the type of measure and the intent of the estimation process.
The hospital weights will be useful for producing hospital-level statistics for analyses that use the hospital as the unit of analysis, and the discharge weights will be useful for producing discharge-level statistics for analyses that use the discharge as the unit of analysis. These would be used to weight the sample data in estimating population statistics.
Several statistical programming packages allow weighted analyses.^{5} For example, nearly all SAS (Statistical Analysis System) procedures incorporate weights.
In addition, several statistical analysis programs have been developed that specifically calculate statistics and their standard errors from survey data. For an excellent review of programs to calculate statistics from survey data, visit the following website: http://www.hcp.med.harvard.edu/statistics/survey-soft/.
The NIS database includes a Hospital Weights file with variables required by these programs to calculate finite population statistics. In addition to the sample weights described earlier, hospital identifiers (PSUs), stratification variables, and stratum-specific totals for the numbers of discharges and hospitals are included so that finite-population corrections (FPCs) can be applied to variance estimates.
In addition to these subroutines, standard errors can be estimated by validation and cross-validation techniques. Given that a very large number of observations will be available for most analyses, it may be feasible to set aside a part of the data for validation purposes. Standard errors and confidence intervals can then be calculated from the validation data. If the analytical file is too small to set aside a large validation sample, cross-validation techniques may be used.
For example, tenfold cross-validation would split the data into ten equal-sized subsets. The estimation would take place in ten iterations. At each iteration, the outcome of interest is predicted for one-tenth of the observations by an estimate based on a model fit to the other nine-tenths of the observations. Unbiased estimates of error variance are then obtained by comparing the actual values to the predicted values obtained in this manner.
Finally, it should be noted that a large array of hospital-level variables are available for the entire universe of hospitals, including those outside the sampling frame. For instance, the variables from the AHA surveys and from the Medicare Cost Reports are available for nearly all hospitals. To the extent that hospital-level outcomes correlate with these variables, they may be used to sharpen regional and nationwide estimates.
As a simple example, each hospital's number of C-sections would be correlated with their total number of deliveries. The number of C-sections must be obtained from discharge data, but the number of deliveries is available from AHA data. Thus, if a regression can be fit predicting C-sections from deliveries based on the NIS data, that regression can then be used to obtain hospital-specific estimates of the number of C-sections for all hospitals in the universe.
As previously shown in Table 0, hospitals that continue in the NIS for multiple consecutive years are a subset of the hospitals in the NIS for any one of those years. Consequently, longitudinal analyses of hospital-level outcomes may be biased if they are based on any subset of NIS hospitals limited to continuous NIS membership. In particular, such subsets would tend to contain fewer hospitals that opened, closed, split, merged, or changed strata. Further, the sample weights were developed as annual, cross-sectional weights rather than longitudinal weights. Therefore, different weights might be required, depending on the statistical methods employed by the analyst.
One approach to consider in hospital-level longitudinal analyses is to use repeated-measure models that allow hospitals to have missing values for some years. However, the data are not actually missing for some hospitals, such as those that closed during the study period. In any case, the analyses may be more efficient (e.g., produce more precise estimates) if they account for the potential correlation between repeated measures on the same hospital over time, yet incorporate data from all hospitals in the sample during the study period.
The two nonoverlapping 10 percent subsamples of discharges were drawn from the NIS file for each year for several reasons pertaining to data analysis. One reason for creating the subsamples was to reduce processing costs for selected studies that will not require the entire NIS. Another reason is that the two subsamples may be used to validate models and obtain unbiased estimates of standard errors. That is, one subsample may be used to estimate statistical models, and the other subsample may be used to test the fit of those models on new data. This is a very important analytical step, particularly in exploratory studies, where one runs the risk of fitting noise.
For example, it is well known that the percentage of variance explained by a regression, R2, is generally overestimated by the data used to fit a model. The regression model could be estimated from the first subsample and then applied to the second subsample. The squared correlation between the actual and predicted value in the second subsample is an unbiased estimate of the model's true explanatory power when applied to new data.
Internet Citation: 1997 NIS Design Report. Healthcare Cost and Utilization Project (HCUP). June 2016. Agency for Healthcare Research and Quality, Rockville, MD. www.hcup-us.ahrq.gov/db/nation/nis/reports/NIS_1997_Design_Report.jsp. |
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Last modified 6/30/16 |