Page 80. where C) refers to estimation cell (defined by industry and, for selected industries, region)
|
|
- Virgil Shelton
- 5 years ago
- Views:
Transcription
1 Nonresponse Adjustment in the Current Statistis Survey 1 Kennon R. Copeland U.S. Bureau of Labor Statistis 2 Massahusetts Avenue, N.E. Washington, DC (Copeland.Kennon@bls.gov) I. Introdution The Bureau of Labor Statistis (BLS) Current Statistis (CES) survey ollets employment, hours, and earnings data monthly from a sample of over 300,000 U.S. establishments. To provide timely information, initial estimates are generated three to four weeks after the survey referene period. Final estimates, inorporating late reports reeived after prodution of the preliminary estimates, are released two months later. Benhmark estimates, inorporating administrative population data from the BLS ES-202 program for Marh of the prior year, are released annually with the data for May. Nonresponse potentially introdues bias into survey estimates, if respondents differ from nonrespondents relative to the variables of interest, and also redues the effetive sample size of a survey, thereby inreasing varianes for survey estimates. Estimation methods are developed so as to aount for nonresponse and lessen its impat on bias and variane. These methods, however, assume nonresponse is ignorable within defined estimation ells and, hene, do not distinguish among various patterns of nonresponse. Nonresponse is used here to enompass both nonreporting and late reporting. Late reporting is temporal nonresponse, as the data beome available at a subsequent point in time. This paper ontinues researh presented in Copeland (2003). Setion II presents a brief overview of the CES survey design, Setion III defines and profiles CES survey reporting patterns, Setion IV examines effets of late reporting and nonresponse on CES survey estimates, and Setion V disusses alternative nonresponse and late reporting adjustment models. II. CES Survey Design The BLS reently ompleted a major redesign of the CES survey (Werking, 1997; Bureau of Labor Statistis, 2003), moving the survey from its historial quota sample design to a probability sampling basis. The new sample design is a stratified, simple random sample of establishments from the BLS s Longitudinal Data Base, with strata defined by state, industry, and employment size. Sampling rates for eah stratum are determined through optimum alloation to minimize variane of total employment level. Data must be reported within a two to three week period for inlusion in the initial published estimates (referred to as first losing estimates) for the month. As additional responses are reeived after this first losing of the olletion period, the estimates for a given month are revised twie (referred to as seond and third losing estimates) to inorporate data from late reporters. The first losing estimate of month-to-month hange is derived by subtrating the prior month s seond losing estimate from the urrent month s first losing estimate. Estimates are generated through use of a weighted link-relative estimator, whih uses a weighted sample trend within an estimation ell, based upon ommon reporters between the prior and urrent months, to move forward the prior month s estimate for that ell. The urrent estimator for total employment (Bureau of Labor Statistis, 2001) takes the following form for month t and losing k = 1,2,3 Yˆ t k = C = 1 i i s t ( ) w iyti s ( ) C t, t 1 k Yˆ ( t ) k + = t ( t ) ky ˆ 1 ( 1), 1 wiy i = 1, k [ ( k + 1) ] where ( = 1,..., C) refers to estimation ell (defined by industry and, for seleted industries, region) s t ( t 1) k, represents the set of sample establishments in estimation ell that, as of losing k, reported data for both months t and t 1 w i is the sampling weight for sample establishment i Y ti is the total employment reported for month t by sample establishment i 1 Any opinions expressed in this paper are those of the author and do not onstitute poliy of the Bureau of Labor Statistis Page 80
2 Y ˆ represents the prior month, t 1, link-relative estimate for estimation ell based upon data reported as of ( t 1) ( k + 1) losing k +1 (with a maximum value of three) for month t 1 (whih orresponds to losing k for month t ) The link-relative,, is thus a growth rate estimate for the period t 1 to t. Differenes in estimates between losings t, ( t 1) will be due solely to the inlusion of late responses, while differenes between estimated and benhmark values will be due to the ombined effets of sampling, nonresponse, late reporting (if omparing first or seond losing estimates), and measurement error. An implit assumption of the estimator is that, within an estimation ell, establishments not reporting data (nonsampled, nonreporting, late reporting) for both months t and t 1 are assumed to have the same growth rate as for those establishments reporting data, i.e., the sampling, response, and reporting timeliness mehanisms are ignorable (Rubin, 1976). III. Reporting Patterns Survey nonresponse is frequently lassified on the basis of reason for nonresponse. Panel surveys add another dimension to the response mehanism, that being response status by survey period. Surveys that publish revised estimates offer yet another dimension to the response mehanism, that being timeliness of reporting. Little and David (1983) distinguished three types of panel survey nonresponse attrition (sample unit stops reporting), late entry (sample unit does not report initially), and reentry (sample unit has a gap in reporting). While this ategorization desribes general patterns of nonresponse, the types are not mutually exlusive. A sample unit that stops reporting (attrition) ould have had gaps in reporting for time periods prior to attrition (reentry) and may not have reported initially (late entry). Little and Su (1989) identified two patterns of panel survey nonresponse monotone (the only type of nonresponse is attrition) and haphazard (nonresponse is either late entry or reentry or both). Although a fully monotone pattern of nonresponse is unlikely, the atual pattern may be approximately monotone (e.g., dropouts in linial trials). Haphazard nonresponse enompasses a wide variety of nonresponse patterns (i.e., Little and David s late entry and reentry panel nonresponse types, as well as any ombination of the three nonresponse types). These two taxonomies ould be refined to reflet more ompletely the nature of reporting patterns. The Little and David taxonomy does not address mixtures of patterns, while the haphazard pattern of Little and Su does not provide distintions among haphazard patterns. Clarifying these distintions ould prove useful, as distributional properties ould differ among patterns. In addition, omplete nonresponse (sample unit never reports) should be added to the list of nonresponse types and omplete response (sample unit always reports) should be added so all sample units are enompassed by the lassifiation. As a result, it may be more appropriate to talk in terms of panel survey reporting patterns rather than nonresponse patterns. There are five basi types of reporting patterns. Basi Reporting Patterns Complete Response unit reports every time period Complete Nonresponse unit does not report for any time period Attrition unit stops reporting after a given time period Late Entry unit begins reporting after the first time period Episodi Nonresponse unit experienes a mixture of reporting and nonreporting An expanded and refined set of reporting patterns for panel surveys an be defined by mixtures of the basi reporting patterns. This taxonomy for reporting patterns, along with illustrations, is provided in Attahment 1. Note that lassifiation of a sample unit in terms of a reporting pattern is temporary, unless the survey has ended and there will be no further time periods for whih data will be olleted. Reporting patterns defined by only one basi pattern may be thought of as first order reporting patterns, while other reporting patterns (based upon a ombination of basi patterns) may be thought of as interation reporting patterns. These reporting patterns are of interest in that distributional properties may differ among the patterns, thereby affeting the assumptions of the underlying estimation model. Table 1 presents the CES survey reporting pattern distribution for four industries for the period Jan 01 - Jun 02, exluding Complete Nonresponse. Complete Response aounts for 47% - 57% of the sample. Other first order reporting patterns (Strit Attrition, Strit Late Entry, Strit Episodi Nonresponse) aount for 34% - 41% of the sample. Attrition (lassified based on observing reporting patterns through De 02) ourred for 12% to 16% of the sample, while some type of episodi nonresponse ourred for 24% - 30% of the sample. (Note: Late entry ould not be distinguished from initiation of new Page 81
3 sample units (whih was arried out on a flow basis); thus, some establishments lassified as late entry may atually belong to the next higher level. In addition, some establishments lassified as attrition may have beome out of business.) Table 1 Reporting Pattern Distributions Seleted Industries, Jan '01 - Jun '02 Manufaturing NAICS 31xx-33xx Wholesale Trade NAICS 42xx-43xx Mining NAICS 1133, 21xx Constrution NAICS 23xx Complete Response 57.0% 49.8% 51.2% 47.4% Strit Attrition 9.3% 11.8% 10.6% 9.4% Strit Late Entry 7.0% 10.5% 10.2% 9.9% Strit Late Entry Attrition 2.1% 3.5% 3.2% 3.5% Attrition with Episodi Nonresponse Late Entry with Episodi Nonresponse Late Entry Attrition with Episodi Nonresponse 4.1% 4.6% 4.2% 5.4% 2.0% 2.8% 2.0% 2.5% 0.6% 0.6% 0.6% 0.4% Strit Episodi Nonresponse 17.8% 16.5% 17.9% 21.5% For omplete nonresponse and attrition, reason for nonresponse (e.g., refusal, nonontat) ould be of interest as it may provide an indiation of the establishment s situation (nonontats may indiate out of business). Reason for episodi nonresponse (e.g., on vaation, data unavailable) may also be of interest for understanding and addressing nonresponse. For a survey suh as the CES survey, in whih estimates are revised several times, late reporting adds another dimension to reporting patterns, as illustrated in Attahment 2. Late reporting units are treated differently than on-time reporters, thus affeting the eligible sample for the first losing link-relative estimator. The key aspet of timeliness of reporting relative to the urrent form of the link-relative estimator is the fat that late reporting establishments that reported (whether on-time or late) the prior month are not utilized in the link-relative estimation for the urrent month. This serves as a omplement to the key aspet of nonreporting relative to the urrent form of the link-relative estimator being the fat that on-time reporters for the urrent month are not utilized in the link-relative estimation if they did not report in the prior month. For the CES survey, timeliness of reporting is an issue for most sample establishments, although not on a ontinual basis. Table 2 presents top-level distribution of frequeny of first-losing reporting for establishments in the Complete Response reporting pattern, for the eighteen-month period Jan 01 Jun 02. The proportion of establishments in the Complete Response reporting pattern that reported on-time every month ranged from 23% to 29% at the industry level, while the proportion of establishments that reported late every month ranged from 1% to 12%. Further lassifiation of timeliness of reporting patterns ould take into aount shorter time frames (perhaps most reent six months), relationship with length of reporting period (e.g., only late when reporting period less than 11 days), and harateristis of the sample establishments (e.g., length of pay period). Table 2 Timeliness of Reporting Pattern Distributions Seleted Industries, Jan '01 - Jun '02 Sample Reporting all Eighteen Months Manufaturing NAICS 31xx-33xx Wholesale Trade NAICS 42xx-43xx Mining NAICS 1133, 21xx Constrution NAICS 23xx Every Month by First 27.7% 22.7% 22.8% 29.1% Months by First 55.4% 53.6% 51.3% 60.3% 6-11 Months by First 10.6% 8.3% 16.2% 8.1% 1-5 Months by First 4.0% 3.1% 7.6% 2.0% No Month by First 2.2% 12.3% 2.1% 0.6% Page 82
4 Copeland (2003) provides additional tabulations of CES survey reporting patterns. The distributional information on reporting patterns and timeliness of reporting indiates: 1) when viewed aross long time periods, inomplete data or late reported data ours for a large proportion of sample establishments; 2) prior CES survey reported employment information is available for many nonreporting/late reporting sample establishments. IV. Impat of Late Reporting and Nonresponse The impat of nonresponse in the CES survey may be examined diretly for late reporting, and indiretly for both late reporting and nonresponse. Comparisons of first and third losing estimates provide a diret indiation of the impat of late reporting, as the only differene between the two estimates is the inlusion of late reporters into the sample. The relative differene between first and third losing estimates for month t, ˆ ˆ Yt 1 Yt 3 RelDiff t( 1,3) = 100% ˆ Y t 3 and the differene between first and third losing estimates of the month-to-month hange from month t 1 to month t, [ 2 ] [ Yˆ t 3 Yˆ 3 ] = t, 1 t, Difft( 1,3) = ˆ t 1 Yˆ Y 3 provide measures of the extent to whih growth rates for late reporters differed from those for early reporters. Large differenes provide an indiation of nonignorability of late reporting. Figure 1 presents relative differenes between first and third losing non-seasonally adjusted estimates of monthly employment for the period May 01 Feb 02 and May 02 Feb 03 for the four industries for whih probability sampling had been implemented as of May Marh and April were exluded from this graph due to the nature of CES survey proessing, with annual benhmark data inorporated with the publiation of first losing estimates for May (and thus seond losing for April and third losing for Marh), and thus negating the ability to measure solely late reporting impat for these months. Although the larger industries have experiened fairly small revisions (absolute relative differenes less than 0.25%), the revisions for Mining have been muh greater, with the absolute relative differene as high as 1.1% in Feb % Figure 1 First Revision, Relative to Third Estimate Seleted Industries: May '01 - Feb '02, May '02 - Feb '03 0.9% Relative Estimate 0.6% 0.3% 0.0% -0.3% -0.6% -0.9% -1.2% Manufaturing Wholesale Trade Mining Constrution May-01 Jun-01 Jul-01 Aug-01 Sep-01 Ot-01 Nov-01 De-01 Jan-02 Feb-02 Mar-02 Apr-02 May-02 Jun-02 Jul-02 Aug-02 Sep-02 Ot-02 Nov-02 De-02 Jan-03 Feb-03 Month Revisions in the monthly employment estimates and in the estimates of month-to-month hange in employment an also be ompared with the month-to-month hange in employment, whih is a primary measure for assessing the employment data. Revisions that are large relative to the estimated hange ould serve to derease the utility of the preliminary reports. Table 3 ompares the magnitudes of the revisions in monthly and month-to-month hange in employment to the first losing estimate of month-to-month hange in employment for the period May 02 Feb 03. Page 83
5 Table 3 First Revisions Relative to First Month-to-Month Change Seleted Industries: May '02 - Feb '03 (Numbers in thousands) Manufaturing Wholesale Trade Mining Constrution (1st ) Change from Prior Month (1st ) Change (1st ) Change from Prior Month (1st ) Change (1st ) Change from Prior Month (1st ) Change (1st ) Change from Prior Month (1st ) May-02 16, , , Change Jun-02 16, , , Jul-02 16, , , Aug-02 16, , , Sep-02 16, , , Ot-02 16, , , Nov-02 16, , , De-02 16, , , Jan-03 16, , , Feb-03 16, , , Although revisions for several months are larger than the first losing estimate of month-to-month employment hange, the hanges in these situations are small. For months with larger employment hanges, revisions are not of the magnitude of the hange, but ould nonetheless be viewed as substantial (five of eighteen first losing hanges of at least 50,000 saw a revision in the first losing estimated employment level that was 10%+ of the magnitude of the first losing estimated hange, while four saw a 10%+ revision in the magnitude of the hange). Viewed from this perspetive, late reporting ould be onsidered to have an impat on the auray of the first losing estimates. A diret indiation of the appropriateness of the assumption of ignorability for late reporting an be made by omparing growth rates for late reporters with those for preliminary reporters. Table 4 provides omparisons of urrent month-to-month growth rates for urrent month first losing reporters and late reporters, for those sample establishments for whih data were available for the prior month. Table 4 Month-to-Month Growth Rates by Current Month Timeliness Status Seleted Industries, Jan '02 - De '02 Establishments with 50+ Manufaturing Wholesale Trade Mining Constrution Month 1st 2nd/3rd 1st 2nd/3rd 1st 2nd/3rd 1st 2nd/3rd Jan '02-0.9% -1.5% -0.9% -0.1% -1.6% -0.6% -4.4% -4.8% Feb ' % -0.7% -0.8% -0.7% -0.8% -1.0% -0.2% -0.9% Mar ' % -0.5% -0.4% -0.3% -0.4% 0.0% 1.0% 1.7% Apr ' % -0.3% 0.2% 0.2% 1.2% 2.8% 2.5% 1.5% May ' % -0.4% 0.0% -0.3% 1.4% 1.0% 1.8% 0.5% Jun '02 0.5% 0.3% 0.1% 0.8% 0.8% -0.5% 2.1% 1.0% Jul '02-0.5% -0.4% -0.1% -0.1% -0.1% -0.3% 0.9% 1.4% Aug '02 0.1% -0.3% -0.3% -0.3% -0.1% 2.5% 0.5% 1.5% Sep '02-0.7% -0.5% 0.2% -0.6% -0.9% -0.8% -1.0% -0.1% Ot '02-0.7% 0.1% -0.1% -0.3% -0.2% 0.0% -0.7% -0.4% Nov '02-0.4% -0.6% -0.4% -0.2% -1.3% -0.6% -2.1% -2.3% De '02-0.2% -0.3% 0.1% -0.5% 0.6% 0.0% -2.6% -2.1% Prior month-to-month growth rates for first losing and late reporters differ by more than one perentage point four times for Mining, three times for Constrution, and no times for Manufaturing and Wholesale Trade. In one instane (for Mining) the differenes are greater than two perentage points. Deriving a rough impat on the overall estimate (aounting for the relative sizes of the first losing and late reporting samples) showed the impat would generally be less than two-tenths of a perentage point, although in some ases the impat ould be greater than seven-tenths of a perentage point. Page 84
6 Assessing the impat of nonresponse is more diffiult, as reported survey data are not available. Although annual benhmark revisions provide an indiation of overall error in the third losing estimates the net result of sampling, nonresponse, and measurement errors nonresponse error annot be isolated from the benhmark results alone. One approah for assessing nonresponse effets would be to use ES-202 data at the establishment level as a proxy for CES survey data, and ompare estimates derived inluding and exluding nonrespondents. An indiret measure of the potential for a nonresponse impat on third losing estimates an also be obtained by omparing prior employment trends between reporters and nonreporters. The urrent estimator assumes nonresponse is ignorable within an estimation ell, and thus makes the implit assumption of equality of month-to-month growth rates for respondents and nonrespondents within an estimation ell. Comparing immediately prior growth rates for urrent period reporters and nonreporters for whih prior data are available provides an indiret indiation of the appropriateness of the equivalene assumption. Table 5 provides omparisons of prior month-to-month growth rates for urrent month reporters and nonreporters, for those sample establishments for whih data were available for the prior two months. Table 5 Prior Month-to-Month Growth Rates by Current Month Reporting Status Seleted Industries, Jan '02 - De '02 Establishments with 50+ Manufaturing Wholesale Trade Mining Constrution Month Nonreporters Reporters Nonreporters Reporters Nonreporters Reporters Nonreporters Reporters Jan '02-0.9% -0.4% -1.1% -0.1% -2.3% -1.0% -2.2% -2.9% Feb ' % -1.1% -1.5% -0.5% -1.0% -1.1% -5.1% -4.4% Mar ' % -0.5% 0.1% -0.8% -3.3% -0.7% 1.6% -0.4% Apr ' % -0.5% -0.2% -0.5% -0.3% -0.5% 1.2% 1.0% May ' % -0.2% 0.2% 0.2% 12.2% 0.8% 3.4% 2.2% Jun '02-0.2% -0.1% 0.4% -0.2% 0.8% 1.2% 0.3% 1.6% Jul '02 0.4% 0.5% 0.6% 0.4% 0.8% 0.4% 2.2% 1.8% Aug '02-0.5% -0.5% 0.3% -0.1% 0.6% -0.2% 2.2% 0.9% Sep '02-1.0% -0.1% -2.4% -0.3% -0.6% 0.9% -0.5% 0.8% Ot '02-0.9% -0.6% -1.5% 0.0% -1.4% -0.8% 0.0% -0.9% Nov '02 0.2% -0.5% -1.3% 0.0% -0.6% -0.1% -0.3% -0.6% De '02-1.1% -0.4% -1.1% -0.2% -2.3% -1.0% -1.6% -2.2% Results show prior month-to-month growth rates for reporters and nonreporters differ by more than one perentage point five times eah for Mining and Constrution, three times for Wholesale Trade, an no times for Manufaturing. In three instanes (twie for Mining and one for Manufaturing) the differenes are greater than two perentage points. Deriving a rough impat on the overall estimate (aounting for the relative sizes of the reporting and nonreporting samples) showed the impat would generally be less than one-tenth of a perentage point, although in some ases the impat ould be greater than eight-tenths of a perentage point. Taken together, these results suggest the implit assumption of equivalene between reporters and nonreporters and of first losing and late reporters may not hold, and that the lak of equivalene may impat both first and third losing estimates. V. Alternative Models The working model that applies to the CES survey estimator of total employment is a proportional regression model, in whih the urrent month s value is assumed proportional to the prior month s value (West, et al, 1989), with the proportionality fator, ρ, assumed to vary by estimation ell, ( = 1, K, C) (whih are ollapsed sample design ells), and month Y = ρ ty + k 2 ( 0, σ Y ) k ~ iid N k ( t 1) This proportional regression model has appeal for use in establishment surveys, where inferene is often made about the rate of hange for the population. In that sense, it an be thought of as a longitudinal analogue to the mean imputation model. However, the weakness of this model lies in its assumption of ignorable nonresponse (for both nonreporters and late reporters) within an estimation ell, and its failure to utilize reported data for establishments other than those reporting for both months t 1 and t. Page 85
7 Review of data from late reporters and nonreporters provided in this paper suggests the ignorability assumption may not always be met. Thus, some refinement to the model may provide opportunities for improvement. Prior researh into ourrene of nonresponse and late reporting (Copeland, 2003) indiates roughly 5% of urrent month first losing reporters are not used in the CES estimator due to lak of data for the prior month, and roughly 15% - 25% of prior month first and seond losing reporters are not used in the CES estimator due to lak of first losing data for the urrent month. Thus, approahes inorporating this urrent information may provide opportunities for improvement. One useful path for further researh would appear to be refinement of estimation ell definitions, in an attempt to define a more appropriate ignorable nonresponse model, using a response propensity approah as desribed in David, et al (1983). Fators for onsideration beyond industry, based upon researh to date, would inlude size of establishment and geography. These fators are utilized in the sample design, but not (with a few exeptions) in the definition of estimation ells. If the estimation ell refinements were to involve suh auxiliary data from the frame, the urrent model ould be ontinued. A seond path would be to explore other ignorable nonresponse models. Auxiliary information known for sample establishments, suh as length of pay period and prior employment hanges may be orrelated with reporting status and/or growth, and therefore be useful in a refined model. However, these auxiliary variables annot be inorporated into the urrent model, as they are not known for the population. One approah would result in imputing for missing values due to late reporters and nonrespondents under a model defined for the sample establishments, with the ompleted sample data file being used to reate link-relative estimates at the ell level as in the urrent approah. The differene would be that all sample establishments, not just those reporting urrent and prior months data, would be used in the estimator. This approah would thus allow use of auxiliary data known only for the sample. A simple model for deriving imputed values would be the urrent proportionality model, with the proportionality fator, ρ, assumed to vary by imputation ell g ( = 1, K, G), defined by a ombination of design and sample auxiliary variables Y tgi = ρ tgy gi + ktgi 2 ( 0, σ Y ) k tgi ~ iid N k gi The proportionality fators ould be estimated from the reporting sample, then used to impute values (using either a deterministi or a stohasti approah) for late reporters and nonreporters. The ompleted data set (reported data for preliminary reporters, imputed values for late reporters and nonrespondents) ould then be used in the urrent link-relative estimator to derive employment estimates. A third path would be to address potential nonignorability of nonresponse. The impat assessment of CES nonreporting and late reporting suggests refinement of the model to allow proportionality fators to vary by reporting pattern within estimation ell. If the assumption of ignorable nonresponse is not used, the question beomes how to estimate the month-to-month employment growth rates (proportionality fators) for nonreporters and late reporters. In addition, if differing proportionality fators are assumed for nonreporters and late reporters, it is neessary to predit whether a nonrespondent at first losing will report late or will be a nonreporter. Little (1993) proposed the use of pattern-mixture models for handling inomplete multivariate data, suh as that arising from a panel survey. Under this approah, models are defined for reporters and nonreporters, with identifying restritions established to allow for estimation of parameters that are non-estimable under the base models. For the CES survey, a simple pattern-mixture approah would be to extend the proportional regression model to allow different growth rates by reporting pattern in the urrent and prior months. Before spefying the model, it is helpful to define two reporting status indiator variables,, for late reporting () and nonreporting (NR). The pair, NR = 0,0, 1,0, 0,1 defines the NR ( { }, ) ( ) ( ) ( ) ( ) th month t reporting status for the i establishment in estimation ell. 1if r = 0 if r 1 3 = 0 and r = 0 or r 3 1 = 1( for month t) = 1(not for month t) NR 1if r = 0 if r 3 3 = 0 (NR for month t) = 1(not NR for month t) where r represents the month t reporting status, as of losing k ( = 1,2,3 ), for establishment i in estimation ell k Page 86
8 A simple extension of the CES model an then be written as Y + k = ρ Y( t 1) ln NR NR NR NR ( ρ ) = ln( ρ ) + 0t + 0t + 1( t 1) ( t 1) + 1( t 1) + e 2 ( 0, ) iid ~ N k k σ 2 ( 0, ) iid ~ N e e σ Note that the approah to assigning reporting status indiator variables also establishes underlying proportionality fators at the estimation ell level, ρ, based upon onsistent preliminary reporters (PR) (i.e., based upon zero values for and NR status in both months). This is analogous to the urrent approah of estimating the proportionality fator for an estimation ell based solely upon PR establishments whih were either PR or in the prior month; however, the extended model reognizes the proportionality fator ould vary for and NR establishments. The oeffients for the reporting status indiators, NR NR 0 t, 0t, 1( t 1), 1( t 1), are not estimable at first losing. Therefore, further assumptions are required for estimation a set of identifying restritions linking the nonestimable parameters to some set of estimable parameters. A simple set of identifying restritions is that the expeted value of the oeffients is invariant over time. + τ 0 t = 0 + τ NR NR 0 t = 0 t NR t = τ 1( t 1) 1 + = τ NR NR NR 1( t 1) 1 + where the τ ' s are assumed normal with mean 0 and onstant variane This model also requires predition of urrent month s reporting status for establishments, given reporting status is only known for first losing reporters. A simple logit preditive model for urrent month s reporting status, based on prior months reporting status may be appropriate. π log π where π π R R( t 1), R( t 2) NR R( t 1), R( t 2) = α + β R( t 1) + β R( t 2) ( = r = 0, R R ) R t, R = P t 1, ( 1) ( 2) 1 ( t 1) ( t 2) = π NR 1 R ( t 1), R( t 2) R( t i), R( t 2 ) 0 if r = 1if r 2 if r = 1(PR) = 0, r 3 = 0 (NR) = 1() This approah an be used, as in the extended ignorable nonresponse approah desribed previously, to impute values for late reporters and nonrespondents and use the ompleted sample data in the weighted link-relative estimator. A more extensive hange would involve imputing values for nonsampled establishments as well, with the resultant omplete population file used to tabulate estimates. Estimation for this model an be arried out through Bayesian analysis utilizing Markov Chains Monte Carlo (MCMC) methods. Evaluation of the performane of the model an be arried out in several ways omparison with third losing Page 87
9 estimates, and omparison with CES benhmark estimates. Based upon the results of a performane analysis of the alternative model, refinements may be proposed and evaluated. An additional hallenge will be model validation; however, this is no different than that faed with the urrent working model. VI. Summary The urrent CES survey estimator of total employment assumes ignorable nonresponse within an estimation ell. Findings suggest that assumption may not always hold and, as a result, employment estimates may be adversely impated. Although the impat may be relatively small, it may be sizeable in terms of employment hange. Further work is needed to evaluate estimation ell definitions and to inorporate information on standard errors of the estimates into the impat assessment. Alternative models, inorporating auxiliary information from sample establishments under an ignorable nonresponse mehanism may provide an opportunity to aount for variability not addressed by the urrent model. Further work is needed to explore the nature of the variability in employment data and to establish and evaluate the performane of appropriate working models addressing this variability. A broad reporting pattern lassifiation that aounts for both reporting status and timeliness of reporting may provide a struture for developing a pattern-mixture model to estimate growth rates without the assumption of ignorable nonresponse. Alternative models would seek to leverage prior information about nonreporters where available, thereby improving upon the urrent working model that only inorporates information about onstant reporters. Further work is needed to explore appliation of the pattern-mixture model with CES survey data, establish a reasonable working model, identify appropriate identifying restritions (espeally where no prior information is available), and determine impat on estimator auray. Referenes Bureau of Labor Statistis. (2001), Chapter 7, Estimation, Current Statistis Manual: U.S. Bureau of Labor Statistis, Washington, D.C. Bureau of Labor Statistis. (2003), BLS Establishment Estimates Revised to Inorporate Marh 2002 Benhmarks, and Earnings: U.S. Bureau of Labor Statistis, Washington, D.C. Copeland, K.R. (2003), Reporting Patterns in the Current Statistis Survey, Proeedings of the Setion on Survey Researh Methods, Amerian Statistial Assoation, (forthoming). David, M.H., Little, R., Samuhel, M., Triest, R. (1983), Imputation Models Based On the Propensity to Respond, Proeedings of the Setion on Business and Eonomi Statistis, Amerian Statistial Assoation, Little, R.J.A. (1993), Pattern-Mixture Models for Multivariate Inomplete Data, Journal of the Amerian Statistial Assoation, 88, Little, R.J.A. and David, M.H. (1983), Weighting Adjustments for Non-response in Panel Surveys, Working paper: U.S. Bureau of the Census, Washington, D.C. Little, R.J.A. and Su, H.-L. (1989), Item Nonresponse in Panel Surveys, in Kasprzyk, D., Dunan, G., Kalton, G., and Singh, M.P. (eds.), Panel Surveys (pp ), New York: John Wiley and Sons, In. Rubin, D.B. (1976), Inferene and Missing Data, Biometrika, 63, Werking, G.S. (1997), Overview of the CES Redesign, Proeedings of the Setion on Survey Researh Methods, Amerian Statistial Assoation, pp West, S., Butani, S., Witt, M., and Adkins, C. (1989), Alternative Imputation Methods for Data, Proeedings of the Setion on Survey Researh Methods, Amerian Statistial Assoation, Page 88
10 Response Pattern Illustrations Shaded area represents data reported for month Month Attahment 1 Response Pattern Classifiation Total Response Total Nonresponse Strit Attrition Strit Late Entry Strit Late Entry Attrition Response Pattern Desription 1 2 t1 t2 T-1 T Unit reports every time period Unit does not report for any time period Unit reports for every time period until some point in time, after whih it no longer reports Unit does not report until some point in time subsequent to the first time period, after whih it ontinues to report for every time period Unit does not report until some point in time subsequent to the first time period, after whih it ontinues to report for every time period until some point in time, after whih it no longer reports Attrition with Episodi Nonresponse Unit reports for the first time period, then experienes a mixture of reporting and nonreporting until some point in time, after whih it no longer reports Late Entry with Episodi Nonresponse Unit does not report until some point in time subsequent to the first time period, after whih it experienes a mixture of reporting and nonreporting for sueeding time periods Late Entry Attrition with Episodi Nonresponse Unit does not report until some point in time subsequent to the first time period, after whih it experienes a mixture of reporting and nonreporting until some point in time, after whih it no longer reports Strit Episodi Nonresponse Unit reports for the first time period, and experienes a mixture of reporting and nonreporting for all subsequent time periods Page 89
11 Timeliness Pattern Illustrations Shaded area represents data reported on-time for month Dotted area represents late reported data for month Month Response Pattern Timeliness Classifiation T-1 T Use Classifiation Current, Prior Month Reporter On-Time both months On-time urrent month only On-time prior month only Late both months Preliminary Preliminary Final Final Attahment 2 Current, Prior Month Nonreporter N/a No Prior Month Only Reporter Current Month Only Reporter On-time Late On-time Late No No No No Page 90
FOREST CITY INDUSTRIAL PARK FIN AN CIAL RETURNS EXECUTIVE SUMMARY
FOREST CITY INDUSTRIAL PARK FIN AN CIAL RETURNS EXECUTIVE SUMMARY The City of London is engagedl in industrial land development for the sole purpose of fostering eonomi growth. The dynamis of industrial
More informationEconomics 2202 (Section 05) Macroeconomic Theory Practice Problem Set 3 Suggested Solutions Professor Sanjay Chugh Fall 2014
Department of Eonomis Boston College Eonomis 2202 (Setion 05) Maroeonomi Theory Pratie Problem Set 3 Suggested Solutions Professor Sanjay Chugh Fall 2014 1. Interation of Consumption Tax and Wage Tax.
More informationValuation of Bermudan-DB-Underpin Option
Valuation of Bermudan-DB-Underpin Option Mary, Hardy 1, David, Saunders 1 and Xiaobai, Zhu 1 1 Department of Statistis and Atuarial Siene, University of Waterloo Marh 31, 2017 Abstrat The study of embedded
More informationStudy on Rural Microfinance System s Defects and Risk Control Based on Operational Mode
International Business and Management Vol. 10, No. 2, 2015, pp. 43-47 DOI:10.3968/6807 ISSN 1923-841X [Print] ISSN 1923-8428 [Online] www.sanada.net www.sanada.org Study on Rural Mirofinane System s Defets
More informationRanking dynamics and volatility. Ronald Rousseau KU Leuven & Antwerp University, Belgium
Ranking dynamis and volatility Ronald Rousseau KU Leuven & Antwerp University, Belgium ronald.rousseau@kuleuven.be Joint work with Carlos Garía-Zorita, Sergio Marugan Lazaro and Elias Sanz-Casado Department
More informationCHAPTER 9 BUDGETARY PLANNING SUMMARY OF QUESTIONS BY STUDY OBJECTIVES AND BLOOM S TAXONOMY. True-False Statements. Multiple Choice Questions
HTER 9 BUDGETARY PLANNING SUMMARY OF QUESTIONS BY STUDY OBJETIVES AND BLOOM S TAXONOMY Item SO BT Item SO BT Item SO BT Item SO BT 4 6 6 6 1 11. 11. 114. 11. 116. 117. 118. 119. 10. 11. 1. 1. 14. 1. 16.
More informationTOTAL PART 1 / 50 TOTAL PART 2 / 50
Department of Eonomis University of Maryland Eonomis 35 Intermediate Maroeonomi Analysis Midterm Exam Suggested Solutions Professor Sanjay Chugh Fall 009 NAME: Eah problem s total number of points is shown
More informationThe Impact of Personal and Institutional Investor Sentiment on Stock. Returns under the Chinese Stock Market Crash. Kexuan Wang
Advanes in Eonomis, Business and Management Researh (AEBMR), volume 26 International Conferene on Eonomis, Finane and Statistis (ICEFS 2017) The Impat of Personal and Institutional Investor Sentiment on
More informationTHE ECONOMIC MOTIVES FOR CHILD ALLOWANCES: ALTRUISM, EXCHANGE OR VALUE OF INDEPENDENCE?
THE EONOMI MOTIVES FOR HILD ALLOWANES: ALTRUISM, EXHANGE OR VALUE OF INDEPENDENE? Lisa Farrell*, Paul Frijters** and Mihael A. Shields* * Department of Eonomis, University of Melbourne, Australia ** Tinbergen
More informationHighlights: 2010 Home Mortgage Disclosure Data
1. Introdution The last five years have seen tremendous hanges in the volume and omposition of mortgage lending in the United States. The impat of Dodd-Frank legislation on the onentration of mortgage
More informationClass Notes: Week 6. Multinomial Outcomes
Ronald Hek Class Notes: Week 6 1 Class Notes: Week 6 Multinomial Outomes For the next ouple of weeks or so, we will look at models where there are more than two ategories of outomes. Multinomial logisti
More informationClipping Coupons: Redemption of Offers with Forward-Looking Consumers
Clipping Coupons: Redemption of Offers with Forward-Looking Consumers Kissan Joseph Oksana Loginova Marh 6, 2019 Abstrat Consumer redemption behavior pertaining to oupons, gift ertifiates, produt sampling,
More informationStrategic Dynamic Sourcing from Competing Suppliers: The Value of Commitment
Strategi Dynami Souring from Competing Suppliers: The Value of Commitment Cuihong Li Laurens G. Debo Shool of Business, University of Connetiut, Storrs, CT0669 Tepper Shool of Business, Carnegie Mellon
More informationState of New Mexico Participation Agreement for Deferred Compensation Plan
State of New Mexio Partiipation Agreement for Deferred Compensation Plan DC-4068 (06/2016) For help, please all 1-866-827-6639 www.newmexio457d.om 1 Things to Remember Please print Payroll Center/Plan
More informationAnalysing the Distributional Impacts of Stablisation Policy with a CGE Model: Illustrations and Critique for Zimbabwe
Analysing the Distributional Impats of Stablisation Poliy with a CGE Model: Illustrations and Critique for Zimbabwe Sonja Fagernäs Eonomi and Statistis Analysis Unit April 2004 ESAU Working Paper 4 Overseas
More informationTariffs and non-tariff measures: substitutes or complements. A cross-country analysis
Bank i Kredyt 48(1), 2017, 45-72 Tariffs and non-tariff measures: substitutes or omplements. A ross-ountry analysis Eyal Ronen* Submitted: 29 April 2016. Aepted: 3 November 2016. Abstrat Alongside the
More informationOptional Section: Continuous Probability Distributions
6 Optional Setion: Continuous Probability Distributions 6.5 The Normal Approximation to the Binomial Distribution For eah retangle, the width is 1 and the height is equal to the probability assoiated with
More informationTransport tax reforms, two-part tariffs, and revenue recycling. - A theoretical result
Transport tax reforms, to-part tariffs, and revenue reyling - A theoretial result Abstrat Jens Erik Nielsen Danish Transport Researh Institute We explore the interation beteen taxes on onership and on
More informationTHE STUDY OF RELATIONSHIP BETWEEN CAPITAL STRUCTURE, FIRM GROWTH WITH FINANCIAL LEVERAGE OF THE COMPANY LISTED IN TEHRAN STOCK EXCHANGE
THE STUDY OF RELATIONSHIP BETWEEN CAPITAL STRUCTURE, FIRM GROWTH WITH FINANCIAL LEVERE OF THE COMPANY LISTED IN TEHRAN STOCK EXCHANGE Fatemeh Arasteh Department of Aounting, Siene and Researh Branh, Islami
More informationPROSPECTUS May 1, Agency Shares
Dreyfus Institutional Reserves Funds Dreyfus Institutional Reserves Money Fund Class/Tiker Ageny shares DRGXX Dreyfus Institutional Reserves Treasury Fund Class/Tiker Ageny shares DGYXX Dreyfus Institutional
More informationOutput and Expenditure
2 Output and Expenditure We begin with stati models of the real eonomy at the aggregate level, abstrating from money, pries, international linkages and eonomi growth. Our ausal perspetive depends on what
More informationWORKING PAPER SERIES 3. Michal Franta The Likelihood of Effective Lower Bound Events
WORKING PAPER SERIES 3 Mihal Franta The Likelihood of Effetive Lower Bound Events WORKING PAPER SERIES The Likelihood of Effetive Lower Bound Events Mihal Franta 3/2018 CNB WORKING PAPER SERIES The Working
More informationAvailability Analysis with Opportunistic Maintenance of a Two Component Deteriorating System
Analysis with Maintenane of a Two Component Deteriorating System Joel P. Varghese and Girish Kumar Abstrat This paper desribes the opportunisti maintenane model for availability analysis of two omponent
More informationConsumption smoothing and the welfare consequences of social insurance in developing economies
Journal of Publi Eonomis 90 (2006) 2351 2356 www.elsevier.om/loate/eonbase Consumption smoothing and the welfare onsequenes of soial insurane in developing eonomies Raj Chetty a,, Adam Looney b a UC-Berkeley
More informationAsymmetric Integration *
Fung and Shneider, International Journal of Applied Eonomis, (, September 005, 8-0 8 Asymmetri Integration * K.C. Fung and Patriia Higino Shneider University of California, Santa Cruz and Mount Holyoke
More informationEcon 455 Answers - Problem Set Consider a small country (Belgium) with the following demand and supply curves for cloth:
Spring 000 Eon 455 Harvey Lapan Eon 455 Answers - Problem Set 4 1. Consider a small ountry (Belgium) with the following demand and supply urves for loth: Supply = 3P ; Demand = 60 3P Assume Belgium an
More informationValue Added Tax (Flat-rate Valuation of Supplies of Fuel for Private Use) Order 2013
Index VALUE ADDED TAX (FLAT-RATE VALUATION OF SUPPLIES OF FUEL FOR PRIVATE USE) ORDER 2013 Index Artile Page 1 Title... 3 2 Commenement... 3 3 Flat-rate basis of valuation of supplies of fuel for private
More informationIS-LM model. Giovanni Di Bartolomeo Macro refresh course Economics PhD 2012/13
IS-LM model Giovanni Di Bartolomeo giovanni.dibartolomeo@uniroma.it Note: These leture notes are inomplete without having attended letures IS Curve Giovanni Di Bartolomeo giovanni.dibartolomeo@uniroma.it
More informationON TRANSACTION COSTS IN STOCK TRADING
QUANTITATIVE METHODS IN ECONOMICS Volume XVIII, No., 07, pp. 58 67 ON TRANSACTION COSTS IN STOCK TRADING Marek Andrzej Koiński Faulty of Applied Informatis and Mathematis Warsaw University of Life Sienes
More information0NDERZOEKSRAPPORT NR TAXES, DEBT AND FINANCIAL INTERMEDIARIES C. VAN HULLE. Wettelijk Depot : D/1986/2376/4
0NDERZOEKSRAPPORT NR. 8603 TAXES, DEBT AND FINANCIAL INTERMEDIARIES BY C. VAN HULLE Wettelijk Depot : D/1986/2376/4 TAXES, DEBT AND FINANCIAL INTERMEDIARIES Muh lending and borrowing is indiret : finanial
More informationThe diversification delta: A different perspective. Author. Published. Journal Title. Version DOI. Copyright Statement.
The diversifiation delta: A different perspetive Author Salazar Flores, Yuri, Bianhi, Robert, Drew, Mihael, Truk, Stefan Published 07 Journal Title Journal of Portfolio Management Version Post-print DOI
More informationTrade Scopes across Destinations: Evidence from Chinese Firm
MPRA Munih Personal RePE Arhive Trade Sopes aross Destinations: Evidene from Chinese Firm Zhuang Miao and Yifan Li MGill University 15 Marh 2017 Online at https://mpra.ub.uni-muenhen.de/80863/ MPRA Paper
More informationEconomics 602 Macroeconomic Theory and Policy Problem Set 4 Suggested Solutions Professor Sanjay Chugh Summer 2010
Department of Applied Eonomis Johns Hopkins University Eonomis 6 Maroeonomi Theory and Poliy Prolem Set 4 Suggested Solutions Professor Sanjay Chugh Summer Optimal Choie in the Consumption-Savings Model
More informationThe Future of Public Employee Retirement Systems
978 0 19 957334 9 Mithell-Main-drv Mithell (Typeset by SPi, Chennai) iii of 343 July 21, 2009 20:23 The Future of Publi Employee Retirement Systems EDITED BY Olivia S. Mithell and Gary Anderson 1 978 0
More informationLimiting Limited Liability
Limiting Limited Liability Giuseppe Dari-Mattiai Amsterdam Center for Law & Eonomis Working Paper No. 2005-05 This paper an be downloaded without harge from the Soial Siene Researh Network Eletroni Paper
More informationT R A D E A N D I N D U S T R I A L P O L I C Y S T R A T E G I E S
Working Paper 1-2004 A Dynami Computable General Equilibrium (CGE) Model for South Afria: Extending the Stati IFPRI Model James Thurlow T R A D E A N D I N D U S T R I A L P O L I C Y S T R A T E G I E
More informationFree Space Path Loss of UWB Communications
Free Spae Path Loss of UWB Communiations Pihaya Supanakoon 1, Sathit Aroonpraparat 1, Sathaporn Promwong 1 and Jun-ihi Takada 1 Department of Information Engineering, Faulty of Engineering, King Mongkut
More informationAUDITING COST OVERRUN CLAIMS *
AUDITING COST OVERRUN CLAIMS * David Pérez-Castrillo # University of Copenhagen & Universitat Autònoma de Barelona Niolas Riedinger ENSAE, Paris Abstrat: We onsider a ost-reimbursement or a ost-sharing
More informationTRADE AND PRODUCTIVITY *
TRADE AND PRODUCTIVITY * FRANCISCO ALCALÁ (UNIVERSIDAD DE MURCIA) AND ANTONIO CICCONE (UNIVERSITAT POMPEU FABRA) November 2003 (forthoming The Quarterly Journal of Eonomis) Abstrat: We find that international
More informationEconomics 325 Intermediate Macroeconomic Analysis Practice Problem Set 1 Suggested Solutions Professor Sanjay Chugh Spring 2011
Department of Eonomis Universit of Marland Eonomis 35 Intermediate Maroeonomi Analsis Pratie Problem Set Suggested Solutions Professor Sanja Chugh Spring 0. Partial Derivatives. For eah of the following
More informationThe Simple Economics of White Elephants
The Simple Eonomis of White Elephants Juan-José Ganuza Universitat Pompeu Fabra and Barelona GSE Gerard Llobet CEMFI and CEPR May 16, 2016 Abstrat This paper disusses how the design of onession ontrats
More informationBonus-Malus System with the Claim Frequency Distribution is Geometric and the Severity Distribution is Truncated Weibull
IOP Conferene Series: Earth and Environmental Siene PAPER OPEN ACCESS Bonus-Malus System with the Claim Frequeny Distribution is Geometri and the Severity Distribution is Trunated Weibull To ite this artile:
More informationOptimal Disclosure Decisions When There are Penalties for Nondisclosure
Optimal Dislosure Deisions When There are Penalties for Nondislosure Ronald A. Dye August 16, 2015 Abstrat We study a model of the seller of an asset who is liable for damages to buyers of the asset if,
More informationNBER WORKING PAPER SERIES MYOPIA AND THE EFFECTS OF SOCIAL SECURITY AND CAPITAL TAXATION ON LABOR SUPPLY. Louis Kaplow
NBER WORKING PAPER SERIES MYOPIA AND THE EFFECTS OF SOCIAL SECURITY AND CAPITAL TAXATION ON LABOR SUPPLY Louis Kaplow Working Paper 45 http://www.nber.org/papers/w45 NATIONAL BUREAU OF ECONOMIC RESEARCH
More informationTHE INCORPORATION OF BUDGET CONSTRAINTS WITHIN STATED CHOICE EXPERIMENTS TO ACCOUNT FOR THE ROLE OF OUTSIDE GOODS AND PREFERENCE SEPARABILITY
THE INCORPORATION OF BUDGET CONSTRAINTS WITHIN STATED CHOICE EXPERIMENTS TO ACCOUNT FOR THE ROLE OF OUTSIDE GOODS AND PREFERENCE SEPARABILITY John Rose 2/26/18 BIDA Working Paper 1801 THE INCORPORATION
More informationImplementing the 2018/19 GP contract
Implementing the 2018/19 GP ontrat Changes to Personal Medial Servies and Alternative Provider Medial Servies ontrats Implementing the 2018/19 GP ontrat Changes to Personal Medial Servies and Alternative
More informationRational Bias in Inflation Expectations
Rational Bias in Inflation Expetations Robert G. Murphy * Boston College Adam Rohde Charles River Assoiates August 2014 Revised August 2015 Abstrat This paper argues that individuals may rationally weight
More informationAt a cost-minimizing input mix, the MRTS (ratio of marginal products) must equal the ratio of factor prices, or. f r
ECON 311 NAME: KEY Fall Quarter, 2011 Prof. Hamilton Final Exam 200 points 1. (30 points). A firm in Los Angeles produes rubber gaskets using labor, L, and apital, K, aording to a prodution funtion Q =
More informationContending with Risk Selection in Competitive Health Insurance Markets
This paper is prepared for presentation at the leture, Sikness Fund Compensation and Risk Seletion at the annual meeting of the Verein für Soialpolitik, Bonn, Germany September 29, 2005. September 19,
More informationResearch Article The Real Causes of Inflation
Current Researh Journal of Eonomi Theory 7(1): 1-10, 2015 ISSN: 2042-4841, e-issn: 2042-485X 2015 Maxwell Sientifi Publiation Corp. Submitted: Otober 12, 2014 Aepted: January 27, 2015 Published: May 20,
More informationEndogenous Peer Effects in School Participation
ndogenous Peer ffets in Shool Partiipation Gustavo J. Bobonis and Frederio Finan Otober 006 Abstrat: A remaining obstale in the literature on peer effets has been the inability to distinguish between peer
More informationThe effect of oil price shocks on economic growth (Case Study; Selected Oil Exporting Countries)
Tehnial Journal of Engineering and Applied Sienes Available online at www.tjeas.om 2013 TJEAS Journal-2013-3-17/2118-2122 ISSN 2051-0853 2013 TJEAS The effet of oil prie shoks on eonomi growth (Case Study;
More informationOn Models for Object Lifetime Distributions
On Models for Objet Lifetime Distributions Darko Stefanović Department of Eletrial Engineering Prineton University Prineton, NJ 8544 darko@am.org Kathryn S. MKinley Department of Computer Siene University
More informationFINANCIAL VOLATILITY AND DERIVATIVES PRODUCTS: A BIDIRECTIONAL RELATIONSHIP
FINANCIAL VOLATILITY AND DERIVATIVES PRODUCTS: A BIDIRECTIONAL RELATIONSHIP Claudiu Tiberiu ALBULESCU Politehnia University of Timişoara Timisoara, Romania laudiu.albulesu@t.upt.ro Daniel GOYEAU University
More informationAn EOQ Model with Parabolic Demand Rate and Time Varying Selling Price
Annals of Pure and Applied Mathematis Vol.,.,, 3-43 ISSN: 79-87X (P),79-888(online) Published on 5 September www.researhmathsi.org Annals of An EOQ Model with Paraboli Demand Rate and ime Varying Selling
More informationExperimentation, Private Observability of Success, and the Timing of Monitoring
Experimentation, Private Observability of Suess, and the Timing of Monitoring Alexander Rodivilov Otober 21, 2016 For the latest version, please lik here. Abstrat This paper examines the role of monitoring
More informationAlfons John Weersink. A thesis submitted in partial fulfillment of the requirements for the degree. Master of Science. Applied Economics.
OPTIMAL REPLACEMENT INTERVAL AND DEPRECIATION METHOD OF A COMBINE ON A REPRESENTATIVE DRYLAND GRAIN FARM IN NORTHCENTRAL MONTANA by Alfons John Weersink A thesis submitted in partial fulfillment of the
More informationManaging Future Oil Revenues in Ghana
IFPRI Disussion Paper 00893 August 2009 Managing Future Oil Revenues in Ghana An Assessment of Alternative Alloation Options Clemens Breisinger Xinshen Diao Rainer Shweikert Manfred Wiebelt Development
More informationD Accounting for management
QU EST IONS ounting for management 17 mins 1.1 Whih of the following statements about qualities of good information is false? It should be relevant for its purposes It should be ommuniated to the right
More informationThe Industry Origins of the US-Japan Productivity Gap
KEO Disussion Paper No. 105 The Industry Origins of the US-Japan Produtivity Gap Dale W. Jorgenson (Harvard University) Koji Nomura (Keio University) February 3, 2007 Revised in June 18, 2007 Abstrat This
More informationDTI, CTI & FTI Methodologies. March 2011
DTI, CTI & FTI Methodologies Marh 2011 Copyright 2011 Alpha Finanial Tehnologies, LLC ( AFT ). All rights reserved. No portion of these materials may be reprodued without the prior written onsent of AFT.
More informationAUTHOR COPY. The co-production approach to service: a theoretical background
Journal of the Operational Researh Soiety (213), 1 8 213 Operational Researh Soiety td. All rights reserved. 16-5682/13 www.palgrave-journals.om/jors/ The o-prodution approah to servie: a theoretial bakground
More informationImportant information about our Unforeseeable Emergency Application
Page 1 of 4 Questions? Call 877-NRS-FORU (877-677-3678) Visit us online Go to nrsforu.om to learn about our produts, servies and more. Important information about our Unforeseeable Emergeny Appliation
More informationRetirement Benefits Schemes (Miscellaneous Amendments) RETIREMENT BENEFITS SCHEMES (MISCELLANEOUS AMENDMENTS) REGULATIONS 2014
Retirement Benefits Shemes (Misellaneous Amendments) Index RETIREMENT BENEFITS SCHEMES (MISCELLANEOUS AMENDMENTS) REGULATIONS 2014 Index Regulation Page 1 Title... 3 2 Commenement... 3 3 Amendment of the
More informationNBER WORKING PAPER SERIES A SIMPLE TEST OF PRIVATE INFORMATION IN THE INSURANCE MARKETS WITH HETEROGENEOUS INSURANCE DEMAND
NER WORKING PAPER SERIES A SIMPLE ES OF PRIVAE INFORMAION IN E INSURANCE MARKES WI EEROGENEOUS INSURANCE DEMAND Li Gan Feng uang Adalbert Mayer Working Paper 16738 http://www.nber.org/papers/w16738 NAIONAL
More informationShould platforms be allowed to charge ad valorem fees?
Should platforms be allowed to harge ad valorem fees? Zhu Wang and Julian Wright November 27 Abstrat Many platforms that failitate transations between buyers and sellers harge ad valorem fees in whih fees
More informationExogenous Information, Endogenous Information and Optimal Monetary Policy
Exogenous Information, Endogenous Information and Optimal Monetary Poliy Luigi Paiello Einaudi Institute for Eonomis and Finane Mirko Wiederholt Northwestern University November 2010 Abstrat Most of the
More informationGENERAL DESCRIPTION OF THE DB GLOBAL SOVEREIGN INDICES
Dated: 20 July 2010 GENERAL DESCRIPTION OF THE DB GLOBAL SOVEREIGN INDICES ALTHOUGH THE INDEX SPONSOR WILL OBTAIN INFORMATION FOR INCLUSION IN OR FOR USE IN THE CALCULATION OF AN INDEX FROM SOURCES WHICH
More informationNeighborhood Peer Effects in Secondary School Enrollment Decisions. Gustavo J. Bobonis and Frederico Finan. Current Version: February 2008
Neighborhood Peer ffets in Seondary Shool nrollment Deisions Gustavo J. Bobonis and Frederio Finan Current Version: February 008 First Version: September 003 Abstrat: This paper identifies neighborhood
More informationSequential Procurement Auctions and Their Effect on Investment Decisions
Sequential Prourement Autions and Their Effet on Investment Deisions Gonzalo isternas Niolás Figueroa November 2007 Abstrat In this paper we haraterize the optimal prourement mehanism and the investment
More informationAccident Severity Prediction Formula for Rail-Highway Crossings
5 ident Severity Predition Formula for Rail-Highway Crossings JOHNS. HTZ STRCT The development of formulas to predit the severity of aidents at publi rail-highway rossings is desribed. The formulas make
More informationVariable Markups and Misallocation in Chinese Manufacturing and Services
Variable Markups and Misalloation in Chinese Manufaturing and Servies Jinfeng Ge Zheng Mihael Song Yangzhou Yuan eember 13, 216 Abstrat Cross-ountry omparison reveals an unusually small servie setor in
More informationRational Bias in Inflation Expectations
Rational Bias in Inflation Expetations Robert G. Murphy * Boston College Adam Rohde Charles River Assoiates August 2014 Revised Deember 2014 Abstrat This paper argues that individuals may rationally weight
More informationState of New Mexico Distribution Request for Deferred Compensation Plan
State of New Mexio Distribution Request for Deferred Compensation Plan DC-4075 (12/2015) For help, please all 1-866-827-6639 www.newmexio457d.om 1 Things to Remember Complete all of the setions on the
More informationDynamic Pricing of Di erentiated Products
Dynami Priing of Di erentiated Produts Rossitsa Kotseva and Nikolaos Vettas August 6, 006 Abstrat We examine the dynami priing deision of a rm faing random demand while selling a xed stok of two di erentiated
More informationThe Simple Economics of White Elephants
The Simple Eonomis of White Elephants Juan-José Ganuza Universitat Pompeu Fabra and Barelona GSE Gerard Llobet CEMFI and CEPR May 13, 2016 Abstrat This paper disusses how the design of onession ontrats
More informationTax-loss Selling and the Turn-of-the-Year Effect: New Evidence from Norway 1
Tax-loss Selling and the Turn-of-the-Year Effet: New Evidene from Norway 1 Qinglei Dai Universidade Nova de Lisboa July 2007 1 Aknowledgement: I would like to thank Kristian Rydqvist at Binghamton University,
More informationDTI, CTI & FTI TM Methodologies. May 2010
DTI, CTI & FTI TM Methodologies May 2010 Copyright 2010 Alpha Finanial Tehnologies, LLC. All rights reserved. No portion of these materials may be reprodued without the prior written onsent of Alpha Finanial
More informationGrowth, Income Distribution and Public Debt
Growth, Inome Distribution and Publi Debt A Post Keynesian Approah João Basilio Pereima Neto José Luis Oreiro Abstrat: The objetive of this paper is to evaluate the long-run impat of hanges in fisal poliy
More informationDamage, Death and Downtime Risk Attenuation in the 2011 Christchurch Earthquake
Damage, Death and Downtime Risk Attenuation in the 2011 Christhurh Earthquake J.B. Mander & Y. Huang Zahry Department of Civil Engineering, Texas A&M University, College Station, TX 77843 USA. 2012 NZSEE
More informationAnnual Return/Report of Employee Benefit Plan
Form 5500 Department of the Treasury Internal Revenue Servie Department of Labor Employee Benefits Seurity Administration Pension Benefit Guaranty Corporation Annual Return/Report of Employee Benefit Plan
More informationVulnerability and Livelihoods before and after the Haiti Earthquake
Poliy Researh Working Paper 5850 WPS5850 Vulnerability and Livelihoods before and after the Haiti Earthquake Damien Éhevin Publi Dislosure Authorized Publi Dislosure Authorized Publi Dislosure Authorized
More informationIdiosyncratic Risk, Aggregate Risk, and the Welfare Effects of Social Security
Disussion Paper No. 18-016 Idiosynrati Risk, Aggregate Risk, and the Welfare Effets of Soial Seurity Daniel Harenberg and Alexander Ludwig Disussion Paper No. 18-016 Idiosynrati Risk, Aggregate Risk, and
More informationKyle Bagwell and Robert W. Staiger. Revised: November 1993
Multilateral Tariff Cooperation During the Formation of Regional Free Trade Areas* Kyle Bagwell and Robert W. Staiger Northwestern University The University of Wisonsin and NBER by Revised: November 1993
More informationAnnual Return/Report of Employee Benefit Plan
Form 5500 Department of the Treasury Internal Revenue Servie Department of Labor Employee Benefits Seurity Administration Pension Benefit Guaranty Corporation Annual Return/Report of Employee Benefit Plan
More informationExogenous Information, Endogenous Information and Optimal Monetary Policy
Exogenous Information, Endogenous Information and Optimal Monetary Poliy Luigi Paiello Einaudi Institute for Eonomis and Finane Mirko Wiederholt Northwestern University January 2011 Abstrat This paper
More informationMyopia and the Effects of Social Security and Capital Taxation on Labor Supply
NELLCO NELLCO Legal Sholarship Repository Harvard Law Shool John M. Olin Center for Law, Eonomis and Business Disussion Paper Series Harvard Law Shool 8-5-006 Myopia and the Effets of Soial Seurity and
More informationMulti-Firm Mergers with Leaders and Followers
Multi-irm Mergers with eaders and ollowers Gamal Atallah 1 University of Ottawa Deember 2011 Department of Eonomis, University of Ottawa, P.O. Box 450, STN. A, Ottawa, Ontario, Canada, 1 gatllah@uottawa.a,
More informationThe Simple Economics of White Elephants
The Simple Eonomis of White Elephants Juan-José Ganuza Universitat Pompeu Fabra and Barelona GSE Gerard Llobet CEMFI and CEPR July 13, 2017 Abstrat This paper shows that the onession model disourages firms
More informationThe Impact of Capacity Costs on Bidding Strategies in Procurement Auctions
Review of Aounting Studies, 4, 5 13 (1999) 1999 Kluwer Aademi Publishers, Boston. Manufatured in The Netherlands. The Impat of Capaity Costs on Bidding Strategies in Prourement Autions JÖRG BUDDE University
More informationCarbon leakage: a mechanism design approach
Carbon leakage: a mehanism design approah Lassi Ahlvik and Matti Liski Otober 5, 2017 Abstrat Polluting firms often press poliy makers to offer ompensations or roll bak regulations by threatening to reloate.
More informationDo Agricultural Subsidies Crowd-out or Stimulate Rural Credit Market Institutions?: The Case of CAP Payments
Do Agriultural Subsidies Crowd-out or Stimulate Rural Credit Market Institutions?: The Case of CAP Payments Pavel Ciaian European Commission (DG Joint Researh Centre); Eonomis and Eonometris Researh Institute
More informationMidyear Change Life Event
Midyear Change Life Event Approved by: Approved date: Offie use only Effetive date: See the Summary Plan Desription for more information on benefits at www.oregon.gov/oha/pebb. Contat information (You
More informationPrices, Social Accounts and Economic Models
Paper prepared for the 10th Global Eonomi Analysis Conferene, "Assessing the Foundations of Global Eonomi Analysis", Purdue University, Indiana, USA, June 2007 Pries, Soial Aounts and Eonomi Models Sott
More informationTitle: Bertrand-Edgeworth Competition, Demand Uncertainty, and Asymmetric Outcomes * Authors: Stanley S. Reynolds Bart J. Wilson
Title: Bertrand-Edgeworth Competition, Demand Unertainty, and Asymmetri Outomes * Authors: Stanley S. Reynolds Bart J. Wilson Department of Eonomis Eonomi Siene Laboratory College of Business & Publi Admin.
More informationInternational Productivity Differences, Infrastructure, and Comparative. Advantage
International Produtivity Differenes, Infrastruture, and Comparative Advantage For Submission to the Review of International Eonomis Manusript 4349 Revised, February 2006 Abstrat This paper provides an
More informationPwC International Business Reorganisations Network Monthly Legal Update
PwC International Business Reorganisations Network Monthly Legal Update Edition 11, November 2017 Contents PriewaterhouseCoopers (Australia) 1 PriewaterhouseCoopers Oy (Finaland) The Finish Supreme Court
More informationTrade and Productivity
Trade and Produtivity by Franiso Alalá Universidad de Muria and Antonio Cione Universitat Pompeu Fabra July 2002 (First Version: May 2001) Abstrat: We estimate the effet of international trade on average
More informationFirst-price equilibrium and revenue equivalence in a sequential procurement auction model
Eon Theory (200) 43:99 4 DOI 0.007/s0099-008-0428-7 RESEARCH ARTICLE First-prie equilibrium and revenue equivalene in a sequential prourement aution model J. Philipp Reiß Jens Robert Shöndube Reeived:
More informationAnnual Return/Report of Employee Benefit Plan
Form 5500 Department of the Treasury Internal Revenue Servie Department of Labor Employee Benefits Seurity Administration Pension Benefit Guaranty Corporation Annual Return/Report of Employee Benefit Plan
More information