ECONOMICS SERIES SWP 2009/10. A Nonlinear Approach to Testing the Unit Root Null Hypothesis: An Application to International Health Expenditures
|
|
- Kristopher Fleming
- 5 years ago
- Views:
Transcription
1 Faculty of Business and Law School of Accounting, Economics and Finance ECONOMICS SERIES SWP 2009/10 A Nonlinear Approach to Testing the Unit Root Null Hypothesis: An Application to International Health Expenditures Paresh Kumar Narayan and Stephan Popp The working papers are a series of manuscripts in their draft form. Please do not quote without obtaining the author s consent as these works are in their draft form. The views expressed in this paper are those of the author and not necessarily endorsed by the School or IBISWorld Pty Ltd.
2 A Nonlinear Approach to Testing the Unit Root Null Hypothesis: An Application to International Health Expenditures Paresh Kumar Narayan, School of Accounting, Economics and Finance, Deakin University. Stephan Popp, Department of Economics, University of Duisburg-Essen, Germany. Abstract In this paper, we examine the unit root null hypothesis for per capita total health expenditures, per capital private health expenditures, and per capital public health expenditures for 29 OECD countries. The novelty of our work is that we use a new nonlinear unit root test that allows for one structural break in the data series. We nd that for around 45 per cent of the countries we are able to reject the unit root hypothesis for each of the three health expenditure series. Moreover, using Monte Carlo simulations, we show that our proposed unit root model has better size and power properties than the widely used ADF and LM type tests. 1 Introduction Over the last decade there has been a surge in research on the time series properties of health expenditures (HE). One traditional branch of health economics research has focused on testing the unit root null hypothesis in health expenditure. Recent contributions to health economics research include examining common structural breaks in health expenditures (Narayan, 2006), convergence of health expenditures (Narayan, 2007; Hitiris, 1997; Barros, 199), and relative 1
3 importance of permanent and transitory shocks in explaining health expenditures (Narayan and Narayan, 200). In this paper, we do not contribute a new topic to health economics, rather we revisit the unit root null hypothesis for health expenditures. Our work here, however, is novel on three fronts. First, we examine the unit root null hypothesis for health expenditures by using a new nonlinear unit root test. It should be noted that in this literature, a nonlinear unit root test has not been used previously. This is an important contribution because, as we show later in the paper, based on Monte Carlo simulations, our new unit root test outperforms the conventional augmented Dickey and Fuller (ADF) and Lagrange Multiplier (LM) type tests used to study health expenditures. In other words, we show that the nonlinear test we use has superior size and power properties. The only work that comes closest to our work is Narayan (200), who examines evidence of asymmetric behaviour of per capita health expenditures. He uses the nonparametric Triples test and nds some evidence of asymmetric behaviour in per capita health expenditures. Second, we depart from the tradition of testing for a unit root in total health expenditures. Our empirical analysis is based on three health expenditure series: total per capita health expenditure, private per capita health expenditure, and public per capita health expenditure. The importance of considering this is sensible in light of the fact that the health care system in OECD countries di ers, based on some combination of private and public funded health care, but with di erent weights for each. 2
4 Our third contribution is that we study a wide range of OECD countries (29 countries) and drawing on the new OECD health dataset ensure that our time series sample is most up-to-date, allowing us to capture the more recent developments in health care systems in these countries. This is important, since recent developments (in terms of innovations and policies) can potentially be a source of structural breaks, which have implications for unit root testing. We organise the rest of the paper as follows. In the next section, we discuss the reasons why it is important to test for unit roots in health expenditures. In section 3, we present our nonlinear unit root test and explain the Monte Carlo design used to conduct size and power properties. In section 4, we discuss the data and results, including a comparison of the small sample performance of our test vis-a-vis the ADF type tests with and without a structural break and the minimum LM unit root test proposed by Lee and Strazicich (2004). In section 5, we provide some concluding remarks. 2 Importance of the unit root null hypothesis While testing the unit root null hypothesis in health expenditures dates back over two decades, dating from the work of Hansen and King (1996), and in this sense it is a traditional research topic, there is lack of understanding on the motivations for testing a unit root null hypothesis. As we will see below there are both economic (theoretical) as well as econometric modelling motivations behind this exercise, yet the absence of this understanding in the health economics 3
5 literature implies that testing the unit root null hypothesis is purely a statistical exercise. In this section, we attempt to dispel this view and make clear the motivation for unit root testing. There are three main reasons for the importance of testing the unit root null hypothesis. First, this hypothesis test pro ers knowledge on whether a shock has a permanent or a transitory e ect on health expenditures. When one rejects the unit root null, thus accepting the alternative hypothesis that there is no unit root, it implies that either the series is mean reverting or trend reverting. In other words, a series is deemed stationary when the unit root null is rejected. For a stationary health series, the implication is as follows. Over the time period for which the null was rejected, any health policies and any macroeconomic news, such as changes in interest rates and/or exchange rates, are interpreted to have a transitory e ect on the health expenditure series. This has implications for business cycles. The way this works is as follows. One branch of research has shown that as income increases health expenditures also tend to increase. In other words, there is clear empirical evidence that a positive association exists between per capita income and per capita health expenditures. Since the transitory component of income (or its growth rate or rst di erence) follows a cyclical pattern, depicting economic expansions and contractions, it follows that a similar pattern of expansions and contractions are likely for the health expenditure series. Second, the unit root null hypothesis has direct implications for the health expenditure convergence hypothesis. For instance, Narayan s (2007) conver- 4
6 gence hypothesis - whereby economies with low levels of health expenditures catch-up over time with economies with high levels of health expenditures - is by construction stochastic. This means that in a time series framework the di erence in health expenditures between any two countries should not contain a unit root. In other words, if the unit root null is accepted, then there is no convergence of health expenditures. Third, the unit root hypothesis has clear implications for econometric modelling. For example, one branch of the health economics literature has examined the long-run relationship (cointegration) between health expenditure and GDP. In testing for cointegration, a pre-requisite is that both variables contain a unit root; in other words, accepting the null hypothesis is a rst step toward conducting a test for a long-run relationship. Failure to accept the null hypothesis would only imply that health expenditures share a short-term relationship with GDP. In a related recent study, Narayan and Narayan (200) examine short-run comovement (common cycles) and long-run co-movement (common trends) among health expenditures. Their work suggests that one can only search for common cycles among stationary health expenditures and common trends among nonstationary health expenditures. So, a test for common cycles and common trends (whose motivations are explained in Narayan and Narayan, 200), requires as a pre-requisite, a test for the unit root null hypothesis. 5
7 3 Econometric Methodology 3.1 Nonlinear unit root test We apply the nonlinear unit root test proposed by Popp (200b). The test is based on the following DGP allowing for a smooth break in level and trend: y t = + t + (L) (DU 0 t + DT 0 t) + u t ; (1) u t = u t 1 + " t ; (2) " t = (L)e t ; e t iid(0; 2 e); (3) where DU 0 t = 1(t > T 0 B ) and DT t = 1(t > T 0 B )(t T B 0 ), 1(:) being the indicator function and T 0 B symbolizing the true break date. The parameters and indicate the magnitude of the level and slope break, respectively. It is assumed that all roots of the lag polynomial (L) lie outside the unit circle. The reduced form of the structural model serves then as test regression and has the following form: y t = y t t + D(T B ) t + DU t 1 + DT t 1 + e t (4) with = (1 ) + ; = (1 ); = ( + ), = ( ) and = : (5) This model allows for a break in level and slope for trending data and is de- 6
8 noted model 2 (M2). To restrict the test to a break in level for trending data (henceforth model 1, M1) we set = 0 in equation (1) and in the test regression (4). The null hypothesis = 1 of a unit root against the alternative hypothesis jj < 1 is tested using the pseudo t-statistic of ^. The form of the test regression is similar to the one used by Perron (1997) and Popp (200a) with the di erence that the regression equation (4) is nonlinear in the relevant coe cients, and. Taking the restrictions in (5) into account by estimating equation (4) using nonlinear least squares as described in Popp (200b) leads to e cient estimation of the coe cients and increases the power of the unit root test. The estimate of the unknown break date is that point in time for which the absolute t-value of ^ is maximised: ^T B = arg max T B jt^(t B )j: (6) The tests by Perron (1997) and Popp (200a) di er in the way they choose the break date. While Perron selects that point in time for which the absolute t-value of the coe cient of the slope dummy DT t is maximized, Popp focuses on the absolute t-value of the coe cient of the impulse dummy D(T B ) t as displayed in equation (6). A feature of both tests is that they permit a break under both the null and the alternative hypotheses. This is in contrast to the test by Zivot and Andrews (ZA, 1992), which only allows for a break under the alternative. Lee and Strazicich (2001) show that the ADF-type tests proposed by Perron 7
9 (1997) and ZA (1992) exhibit spurious rejections when a break occurs under the null hypothesis. Because they assign this shortcoming to the general design principle of the ADF-tests, they follow a di erent route by generalizing the LM unit root test of Schmidt-Phillips (1992) to structural breaks. But as shown by Popp (200a), this is not a common feature of all ADF-type unit root tests and also not of the nonlinear unit root test. 3.2 Monte Carlo design We generate the data to calculate the critical values and conduct the size and power analysis for models 1 and 2 according to equations (1) to (3) by using GAUSS version.0. All simulations are based on 10,000 replications of e t iidn(0; 1) each with T + 50 observations. Afterwards, we discard the rst 50 observations to avoid any e ect of the initial condition. To keep the simulations as concise as possible, we restrict our analysis to the case of a break fraction 0 = TB 0 =T of 0.5. We further assume (L) = 1 for the simulations, which means that the break takes e ect abruptly. The trimming factor is always 0.2 which means that we search for the break between the 20 and 0 percent quantile of the total sample, i.e. T B 2 [0:2T; 0:T ]. The critical values are computed for = 1 and T = 10, 20, 30, 40 and 50 under the assumption that no break has occured, i.e. = 0 for model 1 and = = 0 for model 2, based on equation (1). Critical values for further sample sizes can be found in Popp (200b). The size and power properties are calculated for = 1 and = 0:, respectively. In order to assess the e ect of
10 an increasing break magnitude to the test properties, we vary the level break parameter over the values 0, 3, 5 and 10 for model 1. For model 2, we consider all combinations of the level break sizes 2 f0; 5; 10g and the slope break sizes 2 f0; 2; 6; 10g. 4 Data and empirical results 4.1 Data We use three health expenditure data series obtained from the 2007 OECD health database: total per capita health expenditure, public per capita health expenditure, and private per capita health expenditure. For the empirical analysis, all data are converted into natural logarithmic form. Public health expenditure is expenditure incurred by public funds by the state, regional and local government bodies and social security schemes. By comparison private health care expenditure includes private sources of funds, such as out-of-pocket expenses (both over-the-counter and cost-sharing), private insurance programmes, charities and occupational health care (OECD, 2007). The three data series are in real values measured in local currencies. There are two reasons we prefer to work with local currencies rather than some common currency value, such as the US dollar. First, using local currency value ensures that we avoid any biasness in unit root results emanating from the exchange rate e ect. The unit root test hypothesis, motivated by purchasing power parity, is famous in international economics. Using a series based on say the US dollar 9
11 values, may mean that if one rejects (accepts) the null, this may be a result of the fact that the exchange rate variable was stationary (non-stationary). The second reason is that the health economics literature that uses US dollar denominated expenditure series or PPP based series nd mixed results (see results in Narayan, 2006). This con rms the earlier fear of distortionary e ects. It follows that it is more logical to work with domestic currencies. The data series are plotted in Figures 1 and 2. We notice two features of the data. First, a linear trend is observable in all the three series for all the OECD countries. Second, for most of the series, at least one structural break is also visible. In Table 1, we report the annual growth rates for the three health expenditure series. We observe the following. First, for 19 out of the 29 OECD countries the annual growth rate of total health expenditure, for 14 countries the growth rate of public health expenditures, and for 12 countries the growth rate of private health expenditures have been over 4 per cent per annum. 4.2 Results Critical values The critical values of our nonlinear unit root test for models 1 and 2 are reported in Table 2. As explained earlier, we generate critical values for T = 10, 20, 30, 40, 50. It is shown in Popp (200b) that the critical values of the nonlinear test under the assumption of an unknown and endogenously determined break date and those assuming a known break date both converge to the Dickey- Fuller critical values with increasing sample size. For empirical application, 10
12 we recommend the use of the critical values for exogenously given break dates because it leads to a test with empirical size close to nominal size when a break is present and to a test with high power. These critical values will be used for test decision and are displayed in Table Size and power properties In this section, we compare the size and power properties of our nonlinear structural break unit root tests with existing one break unit root tests used in the applied economics literature. In particular, we compare the performance of our nonlinear test with the Zivot and Andrews (1992), Lee and Strazicich (2004), Popp (200a), and Perron (1997) one structural break unit root test. For the sake of comparison, we also analyse the performance of the conventional Dickey and Fuller (1979) test which does not allow for any structural breaks in the data series. The aim of this comparison of the statistical performance of the tests is to show the strength of our test relative to those that are already available. The results for size and power are generated for both models 1 and 2. The results are based on T = 30, 50, 100 and = 0, 3, 5, 10. The results for model 1 are reported in Table 3. We notice that the empirical size of the ADF test is substantially undersized: with increasing break size and sample size, the empirical size converges to zero. By comparison, the Perron (1997) and the ZA (1992) tests are highly oversized with increasing break size. The LS (2004) and Popp (200a) tests, in contrast, have a nominal size close to the empirical 5 per cent level for medium sized breaks; even for large sized breaks 11
13 when T > 50, the size performance is relatively good. The size properties of our proposed nonlinear test, reported in the last columns of Table 3, suggest that the empirical size is close to the nominal 5 per cent level when a break is present ( > 0) even for small sample sizes, such as when T = 30. In terms of power, all tests show that with increasing sample size the power of the tests increases. Since our break date selection criteria is the same as that used in Popp (200a), the probability of detecting the true break is the same as for the Popp (200a) test. Hence, we compare our results directly with Popp (200a). It should be noted that the power of the nonlinear test is much better than that for Popp (200a). When compared with other tests, it is clear that the nonlinear test detects structural breaks more accurately than existing procedures. The results for the size properties of model 2 are reported in Table 4. We notice that the ADF and the Popp (200a) tests are mostly undersized, while the Perron (1997) and ZA (1992) tests are substantially oversized. The LS (2004) test is undersized in most of the cases, but gets considerably oversized with increasing slope break. The nonlinear test has stable size close to the nominal 5 per cent level. Equally important, the probability of detecting the true break date is close to 100 per cent with the Popp (200a) and the nonlinear test this performance is signi cantly superior to the rest of the one structural break test. In terms of the power of model 2, displayed in Table 5, all tests show high power but this power gain seems to have resulted from signi cant oversizing. The nonlinear test does not su er from this distortionary e ect. 12
14 4.2.3 Unit root test results We report the results from the total per capita health expenditure series in Table 6. The results are obtained from two models: M1 and M2, as explained earlier. The results are organised as follows: column 1 reports the list of countries, column 2 contains the sample size and the resulting number of time series observations is provided in column 3, column 4 reports the test statistic from M1 used to test the unit root null, columns 5 and 6 contain the break date and the break fraction, while column 7 reports the optimal lag lengths. The results from M2 are reported beginning column. The presentation of results for the per capita public health expenditure and per capita private health expenditure in Tables 7 and, respectively, are similarly organised. Beginning with the M1 results from the per capita total health expenditure series, we nd that the unit root null hypothesis is rejected at the 1 per cent level for Austria, Belgium, the Netherlands, and Sweden, at the 5 per cent level for Germany, Luxemburg, Portugal, Switzerland, and the UK, and at the 10 per cent level for Poland. In sum, the null hypothesis is rejected for 10 out of the 29 countries in our sample. Results obtained from the M2 model reveal that the unit root null hypothesis is rejected at the 1 per cent level for Australia, the Czech Republic, and the Netherlands, at the 5 per cent level for the UK, Spain, and Sweden, and at the 10 per cent level for Portugal and Switzerland. In total, the unit root null hypothesis from the M2 model is rejected for eight of the 29 countries. Considering the results from both models, for 13 countries the unit root null is 13
15 rejected. Turning to results obtained from the public health expenditure series shown in Table 7, we nd that the M1 model is able to reject the unit root null hypothesis at the 1 per cent level for Belgium, Hungary, Korea, Luxemburg, the Netherlands, Spain, and Sweden, at the 5 per cent level for the Slovak Republic, and at the 10 per cent level for Iceland, Italy, and Portugal. In sum, the unit root null hypothesis is rejected for 11 out of 29 countries. Results from the M2 model reveal that the unit root null hypothesis is rejected at the 1 per cent level for Hungary, Luxemburg, Spain, and Sweden, and at the 5 per cent level for Iceland, Belgium and Mexico. Results from the M2 model reveal that the unit root null hypothesis can be rejected for seven out of 29 countries. The results from the private health expenditure series are reported in Table. Results from M1 reveal that the unit root null hypothesis is rejected at the 1 per cent level for Canada, Ireland, Norway, and Poland, at the 5 per cent level for Australia, Denmark, and Germany, and at the 10 per cent level for Iceland, Japan, Portugal, and the UK. Taken together, the M1 model reveals that the unit root null hypothesis is rejected for 11 out of 29 countries. Results from M2 indicate that the unit root null hypothesis is rejected at the 1 per cent level for Canada and Ireland, at the 5 per cent level for Iceland, and at the 10 per cent level for Mexico and Germany. In all, for ve out of 29 countries the M2 model is able to reject the unit root null hypothesis. In summary, we observe the following. Models M1 and M2 together reveal 14
16 that the unit root null hypothesis can be rejected at conventional levels of signi cance for 13 out of 29 countries in the case of total health expenditure series, for 12 out of 29 countries in the case of public health expenditures and for 11 out of 29 countries in the case of private health expenditures. In general, then, there is evidence that for around 45 per cent of the countries the health expenditure series (total, private, and public) are stationary, while for just over half of the sample the series are non-stationary Discussion of results Table 9 provides a summary of the results relating to the rejection of the null hypothesis for the three health expenditure series. There are at least two reasons for the mixed results. First, the sample size of data di ers by country and is really dictated by data availability. Second, there is heterogeniety in terms of health systems in these OECD countries. In terms of funding for health-care, there is a considerable di erence in the amount of health-care expenditure across the sample. At the top end, in the United States, Switzerland, Germany and Belgium in 2005 health expenditure as a percentage of GDP was 15.3 per cent, 11.6 per cent, 10.3 per cent and 10.2 per cent respectively. By comparison, at the bottom end, in Ireland and Finland in 2005 health expenditure as a percentage of GDP was 7.5 per cent (OECD, 2007). Another source of heterogeneity between countries is in the relative importance of public and private health funding. The public sector is the main source of health funding in all OECD countries except Greece, Mexico and the United 15
17 States. However, private sector funding is more important in some OECD countries than others; see second last column of Table 1. Narayan and Narayan (200) examined permanent and transitory shocks in health-care expenditure in Canada, Japan, Switzerland, the United Kingdom, and the United States. They found that countries in which private funding dominated health-care expenditure, such as in Canada and the United States, were more likely to experience permanent or long-lasting shocks to health-care expenditure. We do nd this to be the case for the USA, Turkey and Greece where the role of the private sector is relatively high compared with the rest of the OECD countries. For these three countries, we are unable to reject the unit root null hypothesis for any of the three health expenditure series. Narayan and Narayan (200) found that for Japan and the United Kingdom, which have well-established public sectors, transitory shocks were more likely; in other words, health expenditure series for those countries dominated by public spending should be stationary. This is so because it seems that public spending of health care is less impacted by shocks in that shocks tend to have only shortterm e ects. This re ects, in large part, public expectations of a certain level of health-care delivery. On the other hand, private sector health providers react to shocks in a permanent way, implying that they make adjustments in response to shocks, thus shocks end up having long-term e ects. Our results to a large extent support the Narayan and Narayan (200) ndings. 16
18 5 Concluding remarks The goal of this paper was to examine the unit root null hypothesis for health expenditure series for OECD countries. The innovation of our work is threefold: rst, we identify the motivation for undertaking a test for the unit root null hypothesis; second, we depart from the tradition of testing the unit root null hypothesis for only the per capita total health expenditure and consider per capita private and public heath expenditures; and third, for the rst time in this literature, we propose a nonlinear approach to modelling the unit root null hypothesis. We study the size and power properties of our proposed nonlinear structural break unit root test with a range of existing one break unit root tests and con rm its statistically superior performance. Our results suggest that the unit root null hypothesis can be rejected at conventional levels of signi cance for 13 out of 29 countries in the case of total health expenditure series, for 12 out of 29 countries in the case of public health expenditures and for 11 out of 29 countries in the case of private health expenditures. In sum, then, there is evidence that for around 45 per cent of the countries the health expenditure series (total, private, and public) are stationary, while for the rest of the sample the series are non-stationary. The main implications of our ndings are that for at least 45 per cent of the OECD countries, shocks to health expenditures (either total, private or public) have only a transitory e ect. This means that shocks a ect health expenditures for only a short period of time. Given the positive link between per capita incomes and per capita health expenditures, in recessions when income levels 17
19 fall a negative shock to health expenditures then health expenditures will also fall. However, this fall in health expenditures is likely to be only for a short period of time, a behaviour consistent with the business cycle. Our results con rm this for at least 45 per cent of the countries. The second implication of our nding is embedded in econometric modelling, particularly cointegration analysis, where knowledge on the integrational properties of health expenditure series is a pre-requisite for the choice of econometric models and estimation techniques. 1
20 References Barros, P. (199): The black box of health care expenditure growth determinants, Health Economics, 7, Dickey, D., and W. Fuller (1979): Distribution of the Estimators for Autoregressive Time Series With a Unit Root, Journal of the American Statistical Association, 74(366), Hitiris, T. (1997): Health care expenditure and integration in the countries of the European Union, Applied Economics, 29, 1 6. Lee, J., and M. Strazicich (2001): Break Point Estimation and Spurious Rejections with Endogenous Unit Root Tests, Oxford Bulletin of Economics and Statistics, 63(5), (2004): Minimum LM Unit Root Test With One Structural Break, Working Paper 04-17, Department of Economics, Appalachian State University. Narayan, P. (2006): Examining Structural Breaks and Growth Rates in International Health Expenditures, Journal of Health Economics, 25, (2007): Do health expenditures "catch-up"? Evidence from OECD countries, Health Economics, 16, (200): Are health expenditures and GDP characterised by asymmetric behaviour? Evidence from 11 OECD countries, Applied Economics, DOI: /
21 Narayan, P., and S. Narayan (200): The role of permanent and transitory shocks in explaining international health expenditures, Health Economics, DOI: /hec OECD (2007): OECD Health Data. CREDES, OECD, Paris. Perron, P. (1997): Further Evidence on Breaking Trend Functions in Macroeconomic Variables, Journal of Econometrics, 0, Popp, S. (200a): New Innovational Outlier Unit Root Test With a Break at an Unknown Time, Journal of Statistical Computation and Simulation, forthcoming. (200b): A Nonlinear Unit Root Test in the Presence of an Unknown Break, Ruhr Economic Papers 45, Rheinisch-Westfälisches Institut für Wirtschaftsforschung, Essen. Schmidt, P., and P. Phillips (1992): LM Tests for a Unit Root in the Presence of Deterministic Trends, Oxford Bulletin of Economics and Statistics, 54(3), Zivot, E., and D. Andrews (1992): Further Evidence on the Great Crash, the Oil-Price Shock, and the Unit-Root Hypothesis, Journal of Business and Economic Statistics, 10(3),
22 Figure 1: Logarithms of total health expenditure (solid line), public health expenditure (dashed line) and private health expenditure (dotted line) in 15 OECD countries 7 Australia 7 6 Austria 7 6 Belgium Canada Finland Czech Republic France Denmark Germany Greece Hungary Iceland Ireland Italy Japan
23 Figure 2: Logarithms of total health expenditure (solid line), public health expenditure (dashed line) and private health expenditure (dotted line) in 15 OECD countries Korea Luxembourg 7 Mexico Netherlands New Zealand Norway Poland Portugal Slovak Republic Spain Sweden Switzerland Turkey United Kingdom United States
24 Table 1: Annual growth rates (in percent) for total, public and private health expenditure in 30 OECD countries Country Sample TotHE Sample PubHE Sample PriHE AvRatio Range Australia Austria Belgium Canada Czech Republic Denmark Finland France Germany Greece Hungary Iceland Ireland Italy Japan Korea Luxembourg Mexico Netherlands New Zealand Norway Poland Portugal Slovak Republic Spain Sweden Switzerland Turkey UK USA Note: AvRatio is the average ratio of public HE to total HE. Range is the di erence between maximum and minimum ratio. 23
25 Table 2: Critical values of nonlinear unit root test for small samples Model 1 Model 2 T 1% 5% 10% 1% 5% 10%
26 Table 3: Size and power comparison of popular one-break unit root tests; Model 1 T ADF Perron Prob ZA Prob LS Prob Popp Prob NL Prob Prob: Probability of detecting the true break date P ( ^TB = T 0 B ) 25
27 Table 4: Size comparison of popular one-break unit root tests; Model 2 T ADF Perron Prob ZA Prob LS Prob Popp Prob NL Prob Prob: Probability of detecting the true break date P ( ^TB = T 0 B ) 26
28 Table 5: Power comparison of popular one-break unit root tests; Model 2 T ADF Perron Prob ZA Prob LS Prob Popp Prob NL Prob Prob: Probability of detecting the true break date P ( ^TB = T 0 B ) 27
29 Table 6: Results of nonlinear one break unit root test for total health expenditure in 30 OECD countries Country Sample T t M ^ 1 ^T B ^ k t M 2 ^ ^T B ^ k Australia Austria Belgium Canada Czech Republic Denmark Finland France Germany Germany Greece Hungary Iceland Ireland Italy Japan Korea Luxembourg Mexico Netherlands New Zealand Norway Poland Portugal Slovak Republic Spain Sweden Switzerland Turkey UK USA Note: */**/*** denotes signi cance at the 10%/5%/1% level. 2
30 Table 7: Results of nonlinear one break unit root test for public health expenditure in 30 OECD countries Country Sample T t M ^ 1 ^T B ^ k t M 2 ^ ^T B ^ k Australia Austria Belgium Canada Czech Republic Denmark Finland France Germany Germany Greece Hungary Iceland Ireland Italy Japan Korea Luxembourg Mexico Netherlands New Zealand Norway Poland Portugal Slovak Republic Spain Sweden Switzerland Turkey UK USA Note: */**/*** denotes signi cance at the 10%/5%/1% level. 29
31 Table : Results of nonlinear one break unit root test for private health expenditure in 30 OECD countries Country Sample T t M ^ 1 ^T B ^ k t M 2 ^ ^T B ^ k Australia Austria Belgium Canada Czech Republic Denmark Finland France Germany Germany Greece Hungary Iceland Ireland Italy Japan Korea Luxembourg Mexico Netherlands New Zealand Norway Poland Portugal Slovak Republic Spain Sweden Switzerland Turkey UK USA Note: */**/*** denotes signi cance at the 10%/5%/1% level. 30
32 Table 9: Rejection of the null hypothesis Country Total HE Public HE Private HE Australia X - X Austria X - - Belgium X X - Germany X - X Luxemburg X X - Netherlands X X - Poland X - X Portugal X X X Sweden X X - Switzerland X - - UK X - X Czech Rep. X - - Spain X X - Mexico - X X Slovak Rep. - X - Korea - X - Italy - X - Iceland - X X Hungary - X - Canada - - X Denmark - - X Ireland - - X Japan - - X Norway - - X 31
ECONOMICS SERIES SWP 2009/11 A New Unit Root Tes t with Two Structural Breaks in Level and S lope at Unknown Time
Faculty of Business and Law School of Accounting, Economics and Finance ECONOMICS SERIES SWP 2009/11 A New Unit Root Test with Two Structural Breaks in Level and Slope at Unknown Time Paresh Kumar Narayan
More informationVolume 31, Issue 1. Mean-reverting behavior of consumption-income ratio in OECD countries: evidence from SURADF panel unit root tests
Volume 3, Issue Mean-reverting behavior of consumption-income ratio in OECD countries: evidence from SURADF panel unit root tests Shu-Yi Liao Department of Applied Economics, National Chung sing University,
More informationSustainability of balancing item of balance of payment for OECD countries: evidence from Fourier Unit Root Tests
Theoretical and Applied Economics FFet al Volume XXII (2015), No. 3(604), Autumn, pp. 93-100 Sustainability of balancing item of balance of payment for OECD countries: evidence from Fourier Unit Root Tests
More informationAn Improved Panel Unit Root Test Using GLS-Detrending
An Improved Panel Unit Root Test Using GLS-Detrending Claude Lopez 1 University of Cincinnati August 2004 This paper o ers a panel extension of the unit root test proposed by Elliott, Rothenberg and Stock
More informationShortfalls of Panel Unit Root Testing. Jack Strauss Saint Louis University. And. Taner Yigit Bilkent University. Abstract
Shortfalls of Panel Unit Root Testing Jack Strauss Saint Louis University And Taner Yigit Bilkent University Abstract This paper shows that (i) magnitude and variation of contemporaneous correlation are
More informationORGANISATION FOR ECONOMIC CO-OPERATION AND DEVELOPMENT
ORGANISATION FOR ECONOMIC CO-OPERATION AND DEVELOPMENT Pursuant to Article 1 of the Convention signed in Paris on 14th December 1960, and which came into force on 30th September 1961, the Organisation
More informationReal exchange rate behavior in 4 CEE countries using different unit root tests under PPP paradigm
1 Introduction Real exchange rate behavior in 4 CEE countries using different unit root tests under PPP paradigm Ghiba Nicolae 1, Sadoveanu Diana 2, Avadanei Anamaria 3 Abstract. This paper aims to analyze
More informationUnit Roots and Structural Breaks in Panels: Does the Model Specification Matter?
18th World IMACS / MODSIM Congress, Cairns, Australia 13-17 July 2009 http://mssanz.org.au/modsim09 Unit Roots and Structural Breaks in Panels: Does the Model Specification Matter? Felix Chan 1 and Laurent
More informationPurchasing Power Parity and the European Single Currency: Some New Evidence
Christidou-Panagiotidis, 309-323 Purchasing Power Parity and the European Single Currency: Some New Evidence Maria Christidou Theodore Panagiotidis Abstract The effect of the single currency on the Purchasing
More informationParity Reversion of Absolute Purchasing Power Parity Zhi-bai ZHANG 1,a,* and Zhi-cun BIAN 2,b
2016 3 rd International Conference on Economics and Management (ICEM 2016) ISBN: 978-1-60595-368-7 Parity Reversion of Absolute Purchasing Power Parity Zhi-bai ZHANG 1,a,* and Zhi-cun BIAN 2,b 1,2 School
More informationLecture 2: Intermediate macroeconomics, autumn Lars Calmfors
Lecture 2: Intermediate macroeconomics, autumn 2008 Lars Calmfors 1 GDP per capita, percent of OECD average, PPP-adjusted Position 1970 Index Position 1980 Index 1 Switzerland 154 1 USA 140 2 USA 147 2
More informationThreshold effects in Okun s Law: a panel data analysis. Abstract
Threshold effects in Okun s Law: a panel data analysis Julien Fouquau ESC Rouen and LEO Abstract Our approach involves the use of switching regime models, to take account of the structural asymmetry and
More informationFrederick H. Wallace Universidad de Quintana Roo Chetumal, Quintana Roo México
Cointegration Tests of Purchasing Power Parity Frederick H. Wallace Universidad de Quintana Roo Chetumal, Quintana Roo México Revised December 28, 2007 I thank Alan Taylor for providing the data used in
More informationA New Nonlinear Unit Root Test with Fourier Function
MPRA Munich Personal RePEc Archive A New Nonlinear Unit Root est with Fourier Function Burak Güriş Istanbul University October 2017 Online at https://mpra.ub.uni-muenchen.de/82260/ MPRA Paper No. 82260,
More informationTESTING FOR UNIT ROOTS IN PANELS IN THE PRESENCE OF STRUCTURAL CHANGE WITH AN APPLICATION TO OECD UNEMPLOYMENT
ESING FOR UNI ROOS IN PANELS IN HE PRESENCE OF SRUCURAL CHANGE WIH AN APPLICAION O OECD UNEMPLOYMEN Christian J. Murray a and David H. Papell b a Department of Economics, University of Houston, Houston,
More informationVolume 29, Issue 1. On the Importance of Span of the Data in Univariate Estimation of the Persistence in Real Exchange Rates
Volume 29, Issue 1 On the Importance of Span of the Data in Univariate Estimation of the Persistence in Real Exchange Rates Hyeongwoo Kim Auburn University Young-Kyu Moh Texas Tech University Abstract
More informationFrederick Wallace Universidad de Quintana Roo. Abstract
Nonlinear unit root tests of PPP using long-horizon data Frederick Wallace Universidad de Quintana Roo Abstract The Kapetanios, Shin, and Snell (KSS, 2003) test for a nonlinear unit root is used to study
More informationRejection Probabilities for a Battery of Unit-Root Tests
WORKING PAPERS IN ECONOMICS No 568 Rejection Probabilities for a Battery of Unit-Root Tests Authors Florin G. Maican Richard J. Sweeney May 2013 ISSN 1403-2473 (print) ISSN 1403-2465 (online) Department
More informationCointegration tests of purchasing power parity
MPRA Munich Personal RePEc Archive Cointegration tests of purchasing power parity Frederick Wallace Universidad de Quintana Roo 1. October 2009 Online at http://mpra.ub.uni-muenchen.de/18079/ MPRA Paper
More informationModelling structural change using broken sticks
Modelling structural change using broken sticks Paul White, Don J. Webber and Angela Helvin Department of Mathematics and Statistics, University of the West of England, Bristol, UK Department of Economics,
More informationLecture 2: Intermediate macroeconomics, autumn Lars Calmfors
Lecture 2: Intermediate macroeconomics, autumn 2009 Lars Calmfors 1 Topics Production Labour productivity and economic growth The Solow Model Endogenous growth Long-run effects of the current recession
More informationCOINTEGRATION TESTS OF PPP: DO THEY ALSO EXHIBIT ERRATIC BEHAVIOUR? Guglielmo Maria Caporale Brunel University, London
COINTEGRATION TESTS OF PPP: DO THEY ALSO EXHIBIT ERRATIC BEHAVIOUR? Guglielmo Maria Caporale Brunel University, London Christoph Hanck Universität Dortmund September 2006 Abstract We analyse whether tests
More informationExamining the Evidence for Purchasing Power Parity Under the. Current Float by Recursive Mean Adjustment
Examining the Evidence for Purchasing Power Parity Under the Current Float by Recursive Mean Adjustment Hyeongwoo Kim and Young-Kyu Moh Auburn University and Texas Tech University June 2009 Abstract This
More informationThe Information Content of Capacity Utilisation Rates for Output Gap Estimates
The Information Content of Capacity Utilisation Rates for Output Gap Estimates Michael Graff and Jan-Egbert Sturm 15 November 2010 Overview Introduction and motivation Data Output gap data: OECD Economic
More informationTesting Purchasing Power Parity Hypothesis for Azerbaijan
Khazar Journal of Humanities and Social Sciences Volume 18, Number 3, 2015 Testing Purchasing Power Parity Hypothesis for Azerbaijan Seymur Agazade Recep Tayyip Erdoğan University, Turkey Introduction
More informationSt. Gallen, Switzerland, August 22-28, 2010
Session Number: First Poster Session Time: Monday, August 23, PM Paper Prepared for the 31st General Conference of The International Association for Research in Income and Wealth St. Gallen, Switzerland,
More informationPurchasing Power Parity in the 34 OECD Countries: Evidence from Quantile-Based Unit Root Tests with both Smooth and Sharp Breaks
MPRA Munich Personal RePEc Archive Purchasing Power Parity in the 34 OECD Countries: Evidence from Quantile-Based Unit Root Tests with both Smooth and Sharp Breaks Mohsen BAHMANI-OSKOOEE and Tsung-Pao
More informationCalories, Obesity and Health in OECD Countries
Presented at: The Agricultural Economics Society's 81st Annual Conference, University of Reading, UK 2nd to 4th April 200 Calories, Obesity and Health in OECD Countries Mario Mazzocchi and W Bruce Traill
More information1 Regression with Time Series Variables
1 Regression with Time Series Variables With time series regression, Y might not only depend on X, but also lags of Y and lags of X Autoregressive Distributed lag (or ADL(p; q)) model has these features:
More informationAre real GDP levels nonstationary across Central and Eastern European countries?
99 Are real GDP levels nonstationary across Central and Eastern European countries? Pei-Long Shen 1, Chih-Wei Su 2 and Hsu-Ling Chang 3 Abstract This study applies the Sequential Panel Selection Method
More informationHow Well Are Recessions and Recoveries Forecast? Prakash Loungani, Herman Stekler and Natalia Tamirisa
How Well Are Recessions and Recoveries Forecast? Prakash Loungani, Herman Stekler and Natalia Tamirisa 1 Outline Focus of the study Data Dispersion and forecast errors during turning points Testing efficiency
More informationExport Destinations and Input Prices. Appendix A
Export Destinations and Input Prices Paulo Bastos Joana Silva Eric Verhoogen Jan. 2016 Appendix A For Online Publication Figure A1. Real Exchange Rate, Selected Richer Export Destinations UK USA Sweden
More informationInflation Revisited: New Evidence from Modified Unit Root Tests
1 Inflation Revisited: New Evidence from Modified Unit Root Tests Walter Enders and Yu Liu * University of Alabama in Tuscaloosa and University of Texas at El Paso Abstract: We propose a simple modification
More informationA Panel Test of Purchasing Power Parity. under the Null of Stationarity.
A Panel Test of Purchasing Power Parity under the Null of Stationarity. John Hunter * and Mark Simpson Department of Economics, Brunel University, Uxbridge, Middlesex UB8 3PH Abstract Purchasing Power
More informationNonlinearity and Inflation Rate Differential Persistence: Evidence from the Eurozone.
Nonlinearity and Inflation Rate Differential Persistence: Evidence from the Eurozone. Nikolaos Giannellis Department of Economics, University of Ioannina, Ioannina, 5, Greece, email: ngianel@cc.uoi.gr.
More informationCointegration tests of purchasing power parity
MPRA Munich Personal RePEc Archive Cointegration tests of purchasing power parity Frederick Wallace Universidad de Quintana Roo 1. October 2009 Online at https://mpra.ub.uni-muenchen.de/24966/ MPRA Paper
More informationGravity Analysis of Regional Economic Interdependence: In case of Japan
Prepared for the 21 st INFORUM World Conference 26-31 August 2013, Listvyanka, Russia Gravity Analysis of Regional Economic Interdependence: In case of Japan Toshiaki Hasegawa Chuo University Tokyo, JAPAN
More informationThe causal relationship between energy consumption and GDP in Turkey
The causal relationship between energy consumption and GDP in Turkey Huseyin Kalyoncu1, Ilhan Ozturk2, Muhittin Kaplan1 1Meliksah University, Faculty of Economics and Administrative Sciences, 38010, Kayseri,
More informationAnother Look at the Stationarity of Inflation rates in OECD countries: Application of Structural break-garch-based unit root tests
MPRA Munich Personal RePEc Archive Another Look at the Stationarity of Inflation rates in OECD countries: Application of Structural break-garch-based unit root tests OlaOluwa S Yaya Economic and Financial
More informationTechnical Appendix-3-Regime asymmetric STAR modeling and exchange rate reversion
Technical Appendix-3-Regime asymmetric STAR modeling and exchange rate reversion Mario Cerrato*, Hyunsok Kim* and Ronald MacDonald** 1 University of Glasgow, Department of Economics, Adam Smith building.
More informationIntroduction to Modern Time Series Analysis
Introduction to Modern Time Series Analysis Gebhard Kirchgässner, Jürgen Wolters and Uwe Hassler Second Edition Springer 3 Teaching Material The following figures and tables are from the above book. They
More informationAre PPP Tests Erratically Behaved? Some Panel Evidence
Are PPP Tests Erratically Behaved? Some Panel Evidence Guglielmo Maria Caporale a, Christoph Hanck b a Brunel University, London b Universität Dortmund October 5, 2006 Abstract This paper examines whether,
More informationPublic Infrastructure and Economic Growth in Mexico
Public Infrastructure and Economic Growth in Mexico Antonio Noriega Matias Fontenla Universidad de Guanajuato and CIDE April 15, 2005 Abstract We develop a model where investment in infrastructure complements
More informationOil price and macroeconomy in Russia. Abstract
Oil price and macroeconomy in Russia Katsuya Ito Fukuoka University Abstract In this note, using the VEC model we attempt to empirically investigate the effects of oil price and monetary shocks on the
More informationRefinement of the OECD regional typology: Economic Performance of Remote Rural Regions
[Preliminary draft April 2010] Refinement of the OECD regional typology: Economic Performance of Remote Rural Regions by Lewis Dijkstra* and Vicente Ruiz** Abstract To account for differences among rural
More informationUniversity of Macedonia Department of Economics. Discussion Paper Series. On the stationarity of per capita carbon dioxide emissions over a century
ISSN 1791-3144 University of Macedonia Department of Economics Discussion Paper Series On the stationarity of per capita carbon dioxide emissions over a century Maria Christidou, Theodore Panagiotidis
More informationA note on the empirics of the neoclassical growth model
Manuscript A note on the empirics of the neoclassical growth model Giovanni Caggiano University of Glasgow Leone Leonida Queen Mary, University of London Abstract This paper shows that the widely used
More informationLong memory or structural breaks: Can either explain nonstationary real exchange rates under the current oat?
Long memory or structural breaks: Can either explain nonstationary real exchange rates under the current oat? Christopher F. Baum Boston College Chestnut Hill, MA 02467 USA John T. Barkoulas Louisiana
More informationFinite-sample quantiles of the Jarque-Bera test
Finite-sample quantiles of the Jarque-Bera test Steve Lawford Department of Economics and Finance, Brunel University First draft: February 2004. Abstract The nite-sample null distribution of the Jarque-Bera
More informationCointegration Tests Using Instrumental Variables Estimation and the Demand for Money in England
Cointegration Tests Using Instrumental Variables Estimation and the Demand for Money in England Kyung So Im Junsoo Lee Walter Enders June 12, 2005 Abstract In this paper, we propose new cointegration tests
More informationVolume 29, Issue 2. Is Malaysian Stock Market Efficient? Evidence from Threshold Unit Root Tests
Volume 29, Issue 2 Is Malaysian Stock Market Efficient? Evidence from Threshold Unit Root Tests Qaiser Munir School of Business and Economics, Universiti malaysia Sabah Kasim Mansur School of Business
More informationCorporate Governance, and the Returns on Investment
Corporate Governance, and the Returns on Investment Klaus Gugler, Dennis C. Mueller and B. Burcin Yurtoglu University of Vienna, Department of Economics BWZ, Bruennerstr. 72, A-1210, Vienna 1 Considerable
More informationTrends in Human Development Index of European Union
Trends in Human Development Index of European Union Department of Statistics, Hacettepe University, Beytepe, Ankara, Turkey spxl@hacettepe.edu.tr, deryacal@hacettepe.edu.tr Abstract: The Human Development
More informationThe saving and investment nexus for China: evidence from cointegration tests
Applied Economics ISSN: 0003-6846 (Print) 1466-4283 (Online) Journal homepage: http://www.tandfonline.com/loi/raec20 The saving and investment nexus for China: evidence from cointegration tests Paresh
More informationThe Causal Relation between Savings and Economic Growth: Some Evidence. from MENA Countries. Bassam AbuAl-Foul
The Causal Relation between Savings and Economic Growth: Some Evidence from MENA Countries Bassam AbuAl-Foul (babufoul@aus.edu) Abstract This paper examines empirically the long-run relationship between
More informationEnergy Consumption and Economic Growth: Evidence from 10 Asian Developing Countries
J. Basic. Appl. Sci. Res., 2(2)1385-1390, 2012 2012, TextRoad Publication ISSN 2090-4304 Journal of Basic and Applied Scientific Research www.textroad.com Energy Consumption and Economic Growth: Evidence
More informationCointegration and the joint con rmation hypothesis
Cointegration and the joint con rmation hypothesis VASCO J. GABRIEL Department of Economics, Birkbeck College, UK University of Minho, Portugal October 2001 Abstract Recent papers by Charemza and Syczewska
More informationPurchasing power parity: A nonlinear multivariate perspective. Abstract
Purchasing power parity: A nonlinear multivariate perspective Frédérique Bec THEMA, University of Cergy-Pontoise and CREST, France Mélika Ben Salem OEP, Paris-Est University and LEA-INRA (PSE), France
More informationJoint hypothesis speci cation for unit root tests with. a structural break
Joint hypothesis speci cation for unit root tests with a structural break Josep Lluís Carrion-i-Silvestre Grup de Recerca AQR Departament d Econometria, Estadística i Economia Espanyola Universitat de
More informationPURCHASING POWER PARITY BEFORE AND AFTER THE ADOPTION OF THE EURO
THE UNIVERSITY OF TEXAS AT SAN ANTONIO, COLLEGE OF BUSINESS Working Paper SERIES January 15, 2008 0031ECO-106-2008 PURCHASING POWER PARITY BEFORE AND AFTER THE ADOPTION OF THE EURO Su Zhou, Mohsen Bahmani-Oskooee
More informationOutput correlation and EMU: evidence from European countries
1 Output correlation and EMU: evidence from European countries Kazuyuki Inagaki Graduate School of Economics, Kobe University, Rokkodai, Nada-ku, Kobe, 657-8501, Japan. Abstract This paper examines the
More informationProductivity and Convergence Trends in the OECD: Evidence from a Normalized Quadratic Variable Pro t Function
Productivity and Convergence Trends in the OECD: Evidence from a Normalized Quadratic Variable Pro t Function Guohua Feng and Apostolos Serletis y Department of Economics University of Calgary Calgary,
More informationNON-LINEARITIES AND HYSTERESIS IN OECD UNEMPLOYMENT *
A R TIGO RBEE Revista Brasileira de Economia de Empresas Brazilian Journal of Business Economics Vol. 2 - nº 3 Setembro - Dezembro 2002 p. 23-30 NON-LINEARITIES AND HYSTERESIS IN OECD UNEMPLOYMENT * Miguel
More informationSpatial Considerations on the PPP Debate *
Federal Reserve Bank of Dallas Globalization and Monetary Policy Institute Working Paper No. 138 http://www.dallasfed.org/assets/documents/institute/wpapers/213/138.pdf Spatial Considerations on the PPP
More informationeconomic growth is not conducive to a country s overall economic performance and, additionally,
WEB APPENDIX: EXAMINING THE CROSS-NATIONAL AND LONGITUDINAL VARIATION IN ECONOMIC PERFORMANCE USING FUZZY-SETS APPENDIX REASONING BEHIND THE BREAKPOINTS FOR THE SETS ECONOMIC GROWTH, EMPLOYMENT AND DEBT
More informationMore formally, the Gini coefficient is defined as. with p(y) = F Y (y) and where GL(p, F ) the Generalized Lorenz ordinate of F Y is ( )
Fortin Econ 56 3. Measurement The theoretical literature on income inequality has developed sophisticated measures (e.g. Gini coefficient) on inequality according to some desirable properties such as decomposability
More information2017 Source of Foreign Income Earned By Fund
2017 Source of Foreign Income Earned By Fund Putnam Emerging Markets Equity Fund EIN: 26-2670607 FYE: 08/31/2017 Statement Pursuant to 1.853-4: The fund is hereby electing to apply code section 853 for
More informationgrowth in a time of debt evidence from the uk
growth in a time of debt evidence from the uk Juergen Amann June 22, 2015 ISEO Summer School 2015 Structure Literature & Research Question Data & Methodology Empirics & Results Conclusio 1 literature &
More informationThe absolute Gini is a more reliable measure of inequality for time dependent analyses (compared with the relative Gini).
The absolute Gini is a more reliable measure of inequality for time dependent analyses (compared with the relative Gini). Sanghamitra Bandyopadhyay Queen Mary, University of London 1st June 2017 Abstract
More informationInterval-Based Composite Indicators
University of Rome Niccolo Cusano Conference of European Statistics Stakeholders 22 November 2014 1 Building Composite Indicators 2 (ICI) 3 Constructing ICI 4 Application on real data Composite Indicators
More informationCO INTEGRATION: APPLICATION TO THE ROLE OF INFRASTRUCTURES ON ECONOMIC DEVELOPMENT IN NIGERIA
CO INTEGRATION: APPLICATION TO THE ROLE OF INFRASTRUCTURES ON ECONOMIC DEVELOPMENT IN NIGERIA Alabi Oluwapelumi Department of Statistics Federal University of Technology, Akure Olarinde O. Bolanle Department
More informationTHE LONG-RUN DETERMINANTS OF MONEY DEMAND IN SLOVAKIA MARTIN LUKÁČIK - ADRIANA LUKÁČIKOVÁ - KAROL SZOMOLÁNYI
92 Multiple Criteria Decision Making XIII THE LONG-RUN DETERMINANTS OF MONEY DEMAND IN SLOVAKIA MARTIN LUKÁČIK - ADRIANA LUKÁČIKOVÁ - KAROL SZOMOLÁNYI Abstract: The paper verifies the long-run determinants
More informationGLS-based unit root tests with multiple structural breaks both under the null and the alternative hypotheses
GLS-based unit root tests with multiple structural breaks both under the null and the alternative hypotheses Josep Lluís Carrion-i-Silvestre University of Barcelona Dukpa Kim Boston University Pierre Perron
More informationMarkov-Switching Models with Endogenous Explanatory Variables. Chang-Jin Kim 1
Markov-Switching Models with Endogenous Explanatory Variables by Chang-Jin Kim 1 Dept. of Economics, Korea University and Dept. of Economics, University of Washington First draft: August, 2002 This version:
More informationCHAPTER III RESEARCH METHODOLOGY. trade balance performance of selected ASEAN-5 countries and exchange rate
CHAPTER III RESEARCH METHODOLOGY 3.1 Research s Object The research object is taking the macroeconomic perspective and focused on selected ASEAN-5 countries. This research is conducted to describe how
More informationDo real exchange rates really display parity-reverting behavior? In summarizing. An Unbiased Appraisal of Purchasing Power Parity
IMF Staff Papers Vol. 50, No. 3 2003 International Monetary Fund An Unbiased Appraisal of Purchasing Power Parity PAUL CASHIN and C. JOHN MCDERMOTT* Univariate studies of the hypothesis of unit roots in
More informationUnited Nations Environment Programme
UNITED NATIONS United Nations Environment Programme Distr. GENERAL 13 April 2016 EP ORIGINAL: ENGLISH EXECUTIVE COMMITTEE OF THE MULTILATERAL FUND FOR THE IMPLEMENTATION OF THE MONTREAL PROTOCOL Seventy-sixth
More informationCointegration and Tests of Purchasing Parity Anthony Mac Guinness- Senior Sophister
Cointegration and Tests of Purchasing Parity Anthony Mac Guinness- Senior Sophister Most of us know Purchasing Power Parity as a sensible way of expressing per capita GNP; that is taking local price levels
More informationA Markov system analysis application on labour market dynamics: The case of Greece
+ A Markov system analysis application on labour market dynamics: The case of Greece Maria Symeonaki Glykeria Stamatopoulou This project has received funding from the European Union s Horizon 2020 research
More informationThe Bootstrap: Theory and Applications. Biing-Shen Kuo National Chengchi University
The Bootstrap: Theory and Applications Biing-Shen Kuo National Chengchi University Motivation: Poor Asymptotic Approximation Most of statistical inference relies on asymptotic theory. Motivation: Poor
More informationACCESSIBILITY TO SERVICES IN REGIONS AND CITIES: MEASURES AND POLICIES NOTE FOR THE WPTI WORKSHOP, 18 JUNE 2013
ACCESSIBILITY TO SERVICES IN REGIONS AND CITIES: MEASURES AND POLICIES NOTE FOR THE WPTI WORKSHOP, 18 JUNE 2013 1. Significant differences in the access to basic and advanced services, such as transport,
More informationAD HOC DRAFTING GROUP ON TRANSNATIONAL ORGANISED CRIME (PC-GR-COT) STATUS OF RATIFICATIONS BY COUNCIL OF EUROPE MEMBER STATES
Strasbourg, 29 May 2015 PC-GR-COT (2013) 2 EN_Rev AD HOC DRAFTING GROUP ON TRANSNATIONAL ORGANISED CRIME (PC-GR-COT) STATUS OF RATIFICATIONS BY COUNCIL OF EUROPE MEMBER STATES TO THE UNITED NATIONS CONVENTION
More informationTesting for PPP: Should We Use Panel Methods??
Empirical Economics manuscript No. (will be inserted by the editor) Testing for PPP: Should We Use Panel Methods?? Anindya Banerjee 1, Massimiliano Marcellino 2 and Chiara Osbat 3 1 Corresponding author:
More informationPLUTO The Transport Response to the National Planning Framework. Dr. Aoife O Grady Department of Transport, Tourism and Sport
PLUTO 2040 The Transport Response to the National Planning Framework Dr. Aoife O Grady Department of Transport, Tourism and Sport Dublin Economics Workshop 15 th September 2018 The Story of Pluto National
More informationBCT Lecture 3. Lukas Vacha.
BCT Lecture 3 Lukas Vacha vachal@utia.cas.cz Stationarity and Unit Root Testing Why do we need to test for Non-Stationarity? The stationarity or otherwise of a series can strongly influence its behaviour
More informationForecasting the Real Exchange Rates Behavior: An Investigation of Nonlinear Competing Models. Yu Liu and Ruxandra Prodan.
Forecasting the Real Exchange Rates Behavior: An Investigation of Nonlinear Competing Models Yu Liu and Ruxandra Prodan Preliminary draft Abstract: There is a large amount of literature which finds that
More information9) Time series econometrics
30C00200 Econometrics 9) Time series econometrics Timo Kuosmanen Professor Management Science http://nomepre.net/index.php/timokuosmanen 1 Macroeconomic data: GDP Inflation rate Examples of time series
More informationAN EMPIRICAL INVESTIGATION ABOUT RELATIONSHIP BETWEEN INTERNATIONAL TRADE AND TOURIST ARRIVAL: EVIDENCE FROM INDIA
AN EMPIRICAL INVESTIGATION ABOUT RELATIONSHIP BETWEEN INTERNATIONAL TRADE AND TOURIST ARRIVAL: EVIDENCE FROM INDIA Vias GAUTAM The ICFAI University, Dehradun, Uttarahand, India vgautam78@gmail.com Suresh
More informationLadu and Meleddu, International Journal of Applied Economics, 13(1), March 2016, 15-31
15 Productivity, Wage and Inflation Relationship for a Sample of Developed Countries: New Evidence from Panel Cointegration Tests with Multiple Structural s Maria Gabriela Ladu a* & Marta Meleddu b* a
More informationHuman Capital, Technology Diffusion and Total Factor Productivity Growth in Regions
Seminar in International Economics 17 September 2018 Human Capital, Technology Diffusion and Total Factor Productivity Growth in Regions Anja Kukuvec Vienna University of Economics and Business (WU) This
More informationLM threshold unit root tests
Lee, J., Strazicich, M.C., & Chul Yu, B. (2011). LM Threshold Unit Root Tests. Economics Letters, 110(2): 113-116 (Feb 2011). Published by Elsevier (ISSN: 0165-1765). http://0- dx.doi.org.wncln.wncln.org/10.1016/j.econlet.2010.10.014
More informationTests for Cointegration, Cobreaking and Cotrending in a System of Trending Variables
Tests for Cointegration, Cobreaking and Cotrending in a System of Trending Variables Josep Lluís Carrion-i-Silvestre University of Barcelona Dukpa Kim y Korea University May 4, 28 Abstract We consider
More informationMonitoring Euro Area Real Exchange Rates
Monitoring Euro Area Real Exchange Rates Philipp Aschersleben, Martin Wagner and Dominik Wied Abstract We apply the stationarity and cointegration monitoring procedure of Wagner and Wied (2014) to the
More informationExtracting information from noisy time series data
Extracting information from noisy time series data Paul Ormerod (Pormerod@volterra.co.uk) Volterra Consulting Ltd Sheen Elms 135c Sheen Lane London SW14 8AE December 2004 1 Abstract A question which is
More informationGovernment Expenditure and Economic Growth in Iran
International Letters of Social and Humanistic Sciences Online: 2013-09-26 ISSN: 2300-2697, Vol. 11, pp 76-83 doi:10.18052/www.scipress.com/ilshs.11.76 2013 SciPress Ltd., Switzerland Government Expenditure
More informationPanel Cointegration and the Monetary Exchange Rate Model
MPRA Munich Personal RePEc Archive Panel Cointegration and the Monetary Exchange Rate Model Syed A. Basher and Joakim Westerlund 12. September 2008 Online at http://mpra.ub.uni-muenchen.de/10453/ MPRA
More informationA Test of Cointegration Rank Based Title Component Analysis.
A Test of Cointegration Rank Based Title Component Analysis Author(s) Chigira, Hiroaki Citation Issue 2006-01 Date Type Technical Report Text Version publisher URL http://hdl.handle.net/10086/13683 Right
More informationTrending Models in the Data
April 13, 2009 Spurious regression I Before we proceed to test for unit root and trend-stationary models, we will examine the phenomena of spurious regression. The material in this lecture can be found
More informationThe PPP Hypothesis Revisited
1288 Discussion Papers Deutsches Institut für Wirtschaftsforschung 2013 The PPP Hypothesis Revisited Evidence Using a Multivariate Long-Memory Model Guglielmo Maria Caporale, Luis A.Gil-Alana and Yuliya
More informationProjektbereich B Discussion Paper No. B-393. Katrin Wesche * Aggregation Bias in Estimating. European Money Demand Functions.
Projektbereich B Discussion Paper No. B-393 Katrin Wesche * Aggregation Bias in Estimating European Money Demand Functions November 1996 *University of Bonn Institut für Internationale Wirtschaftspolitik
More information