Documentation: | Census 1960 Tracts Only Set |
you are here:
choose a survey
survey
document
chapter
Publisher: U.S. Census Bureau
Survey: Census 1960 Tracts Only Set
Document: | Age at First Marriage (Volume II, Part IV - Subject Reports) |
citation: | U.S. Bureau of the Census. U.S. Census of Population: 1960. Subject Reports, Age at First Marriage. Final Report PC(2)-4D. U.S. Government Printing Office, Washington, D.C. 1966. |
Chapter Contents
For persons in housing units at the time of the 1960 Census, the sampling unit was the housing unit and all its occupants; for persons in group quarters, it was the person. On the first visit to an address, the enumerator assigned a Sample Key Letter (A, B, C, or D) to each housing unit sequentially in the order in which he first visited the units, whether or not he completed an Interview. Each enumerator was given a random key letter to start his assignment, and the order of canvassing was indicated in advance, although these instructions allowed some latitude in the order of visiting addresses. Each housing unit to which the key letter "A" was assigned was designated as a sample unit, and ail persons enumerated in the unit were included in the sample. In every group quarters, the sample consisted of every fourth person in the order listed. The 1960 statistics in this report are based on a sub sample of one-fifth of the original. 25-percent sample schedules. The subsample was selected on the computer, using a stratified systematic sample design. The strata were made up as follows: for persons in regular housing units there were 36 strata, i.e., 9 household size groups by 2 tenure groups by 2 color groups; for persons in group quarters, there were 2 strata, i.e., the 2 color groups.
Although the sampling procedure did not automatically insure an exact 5-percent sample of persons, the Sample Design was unbiased if carried through according to instructions. Generally, for large areas, the deviation from the estimated sample size was found to be quite small. Biases may have arisen, however, when the enumerator failed to follow his listing and sampling instructions exactly.
Although the sampling procedure did not automatically insure an exact 5-percent sample of persons, the Sample Design was unbiased if carried through according to instructions. Generally, for large areas, the deviation from the estimated sample size was found to be quite small. Biases may have arisen, however, when the enumerator failed to follow his listing and sampling instructions exactly.
The statistics based on the 5-percent sample of the 1960 Census returns are estimates that have been developed through the use of a Ratio Estimation procedure.
This procedure was carried out for each of the following 44 groups of persons in each of the sample weighting areas:^{1}
The sample weighting areas were defined as those within a State consisting of central cities of urbanized areas, the remaining portion of urbanized areas not in central cities, urban places not in urbanized areas, or rural areas.
For each of the 44 groups, the ratio of the complete count to the sample count of the population in the group was determined. Each specific sample person in the group was assigned an integral weight so that the sum of the weights would equal the complete count for the group. For example, if the ratio for a group was 20.1, one-tenth of the persons (selected at random) within the group were assigned a weight of 21, and the remaining nine-tenths a weight of 20. The use of such, a combination of integral weights rather than a single fractional weight was adopted to avoid the complications involved in rounding in the final tables. In order to increase the reliability, where there were fewer than 275 persons in the complete count in a group, or where the resulting weight was over 80, groups were combined in a specific order to satisfy both of these two conditions.
These ratio estimates reduce the component of sampling error arising from the variation in the size of household and achieve some of the gains of stratification in the selection of the sample, with the strata being the groups for which separate ratio estimates are computed. The net effect is a reduction In the sampling error and bias of most statistics below what would be obtained by weighting the results of the 5- percent sample by a uniform factor of twenty. The reduction in sampling error will be trivial for some items and substantial for others. A byproduct of this estimation procedure, in general, is that estimates for this sample are generally consistent with the complete count with respect to the total population and for the subdivisions used as groups in the estimation procedure. A more complete discussion of the technical aspects of these ratio estimates is presented in 1960 Censuses of Population and Housing: Procedural History, 1966.
This procedure was carried out for each of the following 44 groups of persons in each of the sample weighting areas:^{1}
Group | Sex, color, and age | Relationship and tenure |
Male white: | ||
1 | Under 5 | |
2 | 5 to 13 | |
3 | 14 to 24 | Head of owner household |
4 | 14 to 24 | Head of renter household |
5 | 14 to 24 | Not head of household |
6-8 | 25 to 44 | Same groups as age group 14 to 24 |
9-11 | 45 and over | Same groups as age group 14 to 24 |
Male nonwhite: | ||
12-22 | Same groups as male white | |
Female white: | ||
23-33 | Same groups as male white | |
Female nonwhite: | ||
34-44 | Same groups as male white |
The sample weighting areas were defined as those within a State consisting of central cities of urbanized areas, the remaining portion of urbanized areas not in central cities, urban places not in urbanized areas, or rural areas.
For each of the 44 groups, the ratio of the complete count to the sample count of the population in the group was determined. Each specific sample person in the group was assigned an integral weight so that the sum of the weights would equal the complete count for the group. For example, if the ratio for a group was 20.1, one-tenth of the persons (selected at random) within the group were assigned a weight of 21, and the remaining nine-tenths a weight of 20. The use of such, a combination of integral weights rather than a single fractional weight was adopted to avoid the complications involved in rounding in the final tables. In order to increase the reliability, where there were fewer than 275 persons in the complete count in a group, or where the resulting weight was over 80, groups were combined in a specific order to satisfy both of these two conditions.
These ratio estimates reduce the component of sampling error arising from the variation in the size of household and achieve some of the gains of stratification in the selection of the sample, with the strata being the groups for which separate ratio estimates are computed. The net effect is a reduction In the sampling error and bias of most statistics below what would be obtained by weighting the results of the 5- percent sample by a uniform factor of twenty. The reduction in sampling error will be trivial for some items and substantial for others. A byproduct of this estimation procedure, in general, is that estimates for this sample are generally consistent with the complete count with respect to the total population and for the subdivisions used as groups in the estimation procedure. A more complete discussion of the technical aspects of these ratio estimates is presented in 1960 Censuses of Population and Housing: Procedural History, 1966.
^{1} Estimates of characteristics from the sample for a given area are produced using the formula
Where x' is the estimate of the characteristic for the area obtained through the use of the Ratio Estimation procedure,
x_{i} is the count of sample persons with the characteristic for the area in one (i) of the 44 groups,
y_{i} is the count of all sample persons for the area in the same one of the 44 groups, and
Y_{i} is the count of persons in the complete count for the area in the same one of the 44 groups.
Where x' is the estimate of the characteristic for the area obtained through the use of the Ratio Estimation procedure,
x_{i} is the count of sample persons with the characteristic for the area in one (i) of the 44 groups,
y_{i} is the count of all sample persons for the area in the same one of the 44 groups, and
Y_{i} is the count of persons in the complete count for the area in the same one of the 44 groups.
The figures from the 5-percent sample tabulations are subject to Sampling Variability, which can be estimated roughly from the standard errors shown in tables H and J below.
Table H. Rough Approximation to Standard Error of Estimated Number
Table J. Rough Approximation to Standard Error of Estimated Percentage
(Range of 2 chances out of 3)
These tables^{2} do not reflect the effect of response variance, processing variance, or bias arising in the collection, processing, and estimation steps. Estimates of the magnitude of some of these factors in the total error are being evaluated and will be published at a later date. The chances are about two out of three that the difference due to Sampling Variability between an estimate and the figure that would have been obtained from a complete count of the population is less than the standard error. The chances are about 19 out of 20 that the difference is less than twice the standard error and about 99 out of 100 that it is less than 2 Â½ times the standard error. The amount by which the estimated standard error must be multiplied to obtain other odds deemed more appropriate can be found in most statistical textbooks.
Table H shows rough standard errors of estimated numbers up to 50,000. The relative sampling errors of larger estimated numbers are somewhat smaller than for 50,000. For estimated numbers above 50,000, however, the nonsampling errors, e.g., response errors and processing errors, may have an. increasingly Important effect on the total error. Table J shows rough standard errors of data in the form of percentages. Linear interpolation in tables H and J will provide approximate results that are satisfactory for most purposes.
For a discussion of the Sampling Variability of medians and means and of the method for obtaining standard errors of differences between two estimates, see 1960 Census of Population, Volume I, Characteristics of the Population, Part 1, United States Summary.
Illustration: Table 1.5 shows that there were 35,800 men married 1 year who were sons of the household head, and married with wife present. Linear interpolation in table H shows that an approximation to the standard error for an estimate of 35,800 is 732. This means that the chances are 2 out of 3 that the results of a complete count of all men married 1 year who were sons of the household head and married with wife present, would not differ by more than 732 from a sample estimate. Furthermore, the chances are about 99 in 100 that the difference is less than 1,830 which is 2 ½ times the standard error determined from table H.
Table H. Rough Approximation to Standard Error of Estimated Number
Estimated number | Standard error | |
50 | 30 | |
100 | 40 | |
250 | 60 | |
500 | 90 | |
1,000 | 120 | |
2,500 | 200 | |
5,000 | 280 | |
10,000 | 390 | |
15,000 | 480 | |
25,000 | 620 | |
50,000 | 880 |
Table J. Rough Approximation to Standard Error of Estimated Percentage
(Range of 2 chances out of 3)
Estimated percentage | Base of percentage | |||||
500 | 1,000 | 2,500 | 10,000 | 25,000 | 100,000 | |
2 or 98 | 3.3 | 2.3 | 1.3 | 0.8 | 0.3 | 0.3 |
5 or 95 | 5.0 | 4.0 | 2.3 | 1.0 | 0.5 | 0.3 |
10 or 90 | 7.0 | 5.0 | 3.0 | 1.5 | 0.8 | 0.5 |
25 or 75 | 10.0 | 6.8 | 3.8 | 1.8 | 1.0 | 0.5 |
50 | 11.0 | 7.8 | 4.0 | 2.0 | 1.3 | 0.8 |
These tables^{2} do not reflect the effect of response variance, processing variance, or bias arising in the collection, processing, and estimation steps. Estimates of the magnitude of some of these factors in the total error are being evaluated and will be published at a later date. The chances are about two out of three that the difference due to Sampling Variability between an estimate and the figure that would have been obtained from a complete count of the population is less than the standard error. The chances are about 19 out of 20 that the difference is less than twice the standard error and about 99 out of 100 that it is less than 2 Â½ times the standard error. The amount by which the estimated standard error must be multiplied to obtain other odds deemed more appropriate can be found in most statistical textbooks.
Table H shows rough standard errors of estimated numbers up to 50,000. The relative sampling errors of larger estimated numbers are somewhat smaller than for 50,000. For estimated numbers above 50,000, however, the nonsampling errors, e.g., response errors and processing errors, may have an. increasingly Important effect on the total error. Table J shows rough standard errors of data in the form of percentages. Linear interpolation in tables H and J will provide approximate results that are satisfactory for most purposes.
For a discussion of the Sampling Variability of medians and means and of the method for obtaining standard errors of differences between two estimates, see 1960 Census of Population, Volume I, Characteristics of the Population, Part 1, United States Summary.
Illustration: Table 1.5 shows that there were 35,800 men married 1 year who were sons of the household head, and married with wife present. Linear interpolation in table H shows that an approximation to the standard error for an estimate of 35,800 is 732. This means that the chances are 2 out of 3 that the results of a complete count of all men married 1 year who were sons of the household head and married with wife present, would not differ by more than 732 from a sample estimate. Furthermore, the chances are about 99 in 100 that the difference is less than 1,830 which is 2 ½ times the standard error determined from table H.